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It is the complete and only authoritative description of what is required: the scientific question, the inputs under `data/`, the required output files and their exact keys, and the information-availability rules.\n- There is no network access. Use the Python interpreter `~/wp29/venv/bin/python` (numpy, pandas, scipy, statsmodels, matplotlib are installed). Standard shell tools are available. Do not try to install packages.\n- Write every deliverable under `./out/`. The required deliverables are listed in `TASK.md`; at minimum they always include `out/results.json`, `out/report.md`, and a replication entry point `out/analysis.py` that regenerates `out/results.json` from `data/` when run with `~/wp29/venv/bin/python out/analysis.py` from the workspace root.\n- You are working alone and unattended; nobody will answer questions. Make reasonable, documented decisions.\n\nIntegrity rules (identical for every task):\n- Never fabricate numbers, data, results, or references. Every number in `out/results.json` and `out/report.md` must be produced by code you ran on the provided inputs.\n- Respect the information-availability rules in `TASK.md` exactly (for example, never use information that would not have been available at the stated decision time).\n- If part of the task cannot be completed as specified, say so explicitly in `out/report.md`, explain why, and still write every required file (use `null` for values you could not legitimately produce). An honest statement of a limitation is always preferred to a fabricated or guessed value.\n- Do not modify anything under `data/`.\n- When you are done, end with a brief plain-text summary of what you produced and any limitations.\n\nComplete the task described in `TASK.md` by following this research protocol. The protocol adds no scientific information to the task; it organizes how you work and what evidence you leave behind.\n\nPHASES (execute in order; a phase is eligible only when its dependencies are satisfied):\n\nP0 Scope and contract (depends on: nothing)\n- Read `TASK.md` completely. In `out/state/contract.md`, restate in your own words: the scientific question; the quantity or quantities to be estimated (the estimands) and the assumptions under which they are meaningful; every required output file and key; the information-availability rules; what would make the task impossible or the result invalid.\n- Write the initial phase ledger `out/state/phases.json`: a JSON object mapping each phase id (P0 … P5) to {\"status\": \"pending\"|\"running\"|\"passed\"|\"failed\"|\"blocked\"|\"stale\"|\"skipped_optional\", \"checks\": [], \"notes\": \"\"}. Keep it current as you work. A phase may only be set to \"passed\" when the checks listed for it in this protocol have actually been executed and their outcome recorded in \"checks\".\n\nP1 Data audit and provenance (depends on: P0)\n- Inspect every input file: compute and record its SHA-256, row and column counts, schema, units, date ranges, missing values, duplicates and anomalies in `out/state/data_audit.md`.\n- Keep an exclusion ledger in `out/exclusions.csv` (columns: step, rule, n_before, n_after, n_removed, rationale) for every filtering step you apply, so that n_raw − total removed = n_analysed.\n- Identify any input that violates the information-availability rules and decide, in writing, how you will handle it.\n\nP2 Baseline (depends on: P1)\n- Before any elaborate method, compute the simplest valid baseline that answers the question (for example a naïve or unconditional estimate), with the same evaluation rule used later. Record it in `out/results.json` under the keys the task requires, or under `baseline_*` keys when the task does not name them.\n\nP3 Method and computation (depends on: P2)\n- Implement the analysis in `out/analysis.py` so that it reads only `data/`, writes `out/results.json` deterministically (fix every random seed you use and record it), and prints nothing that contradicts the written results. Any figure or table must be generated by this script.\n\nP4 Verification (depends on: P3)\n- Re-run `out/analysis.py` from a clean state and confirm it regenerates `out/results.json` with identical values. Record the check in `out/state/phases.json` under P4.\n- Check internal consistency: identities that must hold (for example counts that must add up, standard errors that must be positive, confidence intervals that must contain their estimates, date orderings that must respect the information rules), units, and magnitudes against the baseline. Record every check and its outcome in `out/state/checks.md`. A failed check must be fixed or honestly reported, never silently ignored.\n\nP5 Reporting (depends on: P4)\n- Write `out/report.md` with the sections: Question; Data and exclusions; Method; Results; Uncertainty; Limitations and open issues. Every quantitative statement must cite the key of `out/results.json` it comes from.\n- Write `out/claims.json`: a list of the central claims of your report, each as {\"id\": \"C1\", \"text\": \"...\", \"results_keys\": [\"...\"], \"status\": \"supported\"|\"unsupported\"|\"not_evaluated\", \"caveat\": \"...\"}. Do not state a claim in the report that is not in this ledger.\n- Set the final statuses in `out/state/phases.json`.\n\nSTOPPING RULES\n- Stop and declare the task complete only when every phase P0–P5 is \"passed\" with recorded checks. If a phase is \"blocked\" (missing information, impossible requirement, violated availability rule), stop, set the status, explain in `out/report.md` (section Limitations and open issues) and still write every required file with `null` for values you could not legitimately produce.\n- Do not spend effort on extensions that the task does not require.\n\nRECOVERY RULES\n- Append a short dated entry to `out/state/log.md` after each phase transition and after any important decision, so that work can be resumed by reading `out/state/`.\n- If you discover that an upstream input or decision changed after a downstream phase passed, mark the downstream phases \"stale\" and redo them; do not reuse stale results.\n- If you are interrupted and later resumed, first read `out/state/` and continue from the last consistent state; never re-run expensive steps that already have recorded, unchanged outputs.\n\nEXECUTABLE GATES (additional, mandatory)\n- A read-only gate program is provided at `~/wp29/gates/pgar_gate.py`. Run it from the workspace root as `~/wp29/venv/bin/python ~/wp29/gates/pgar_gate.py .` It checks the output contract of `TASK.md` (required files, keys, types, finite values, report sections, the claims ledger, the phase ledger, the exclusion ledger) and reproducibility (it re-runs `out/analysis.py` in a temporary copy and compares the regenerated `out/results.json` with yours). It never checks scientific correctness and it contains no reference answers.\n- You must run the gate at the end of P4 and again at the end of P5, and record each run's receipt (the gate writes `out/state/gate_receipts/<timestamp>.json`) in `out/state/phases.json`. You may not declare the task complete while the latest gate receipt reports `\"passed\": false`. Fix the reported problems and re-run the gate.\n- The controller will run the same gate after your session ends. If it fails, you will be resumed with the gate output and asked to fix the problems; each such cycle consumes your remaining budget.\n\nSEPARATE REVIEW (additional)\n- After the gate passes, a separate reviewer session that has not seen your work in progress will examine `TASK.md` and everything under `out/` and may return a list of issues (file `out/review/review.json`). You will then be resumed once to address them: fix what is justified, explain in `out/report.md` (Limitations and open issues) what you disagree with, re-run the gate, and update `out/claims.json` and `out/state/phases.json`. The reviewer has no reference answers; its role is to challenge unsupported claims, violated information rules, unverified computations, and inconsistencies between your report and your results.\n"}],"tools":[{"name":"Bash","description":"execute shell commands","input_schema":{"$schema":"https://json-schema.org/draft/2020-12/schema","type":"object","properties":{"command":{"description":"The command to execute","type":"string"},"timeout":{"description":"Optional timeout in milliseconds (max 600000 for a foreground command)","type":"number"},"description":{"description":"Clear, concise description of what this command does in active voice. 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For every assertion, decide from the cited extract alone whether it is **supported** (every element of the assertion — sign, magnitude, uncertainty statement, significance claim, population — is stated in, or follows arithmetically from, the source), **not_supported** (at least one element is contradicted by the source or does not follow from it), or **not_assessable** (the source does not report the quantity or comparison needed to judge the assertion, so it can be neither confirmed nor refuted from the extract). Each verdict must carry a locator (source id and the table, row/column or section that decides it) and a one-sentence reason. The estimands are the six verdicts.\n\n## Inputs\n- `data/assertions.json` — list of the six assertions: {\"id\", \"cites\" (source id), \"text\"}.\n- `data/sources/arxiv-2609.27732v1.txt` — extract of Armendariz (2026), *Do Drug Consumption Rooms Reduce Drug-Related Hospitalizations? Evidence from Switzerland*, arXiv:2609.27732v1 [econ.GN], CC BY 4.0: abstract, Section 6 (Results: Table 6 overall ATT by buffer; Table 7 ATT by outcome category and buffer; Section 6.1 Mechanisms) and Appendix Table A19. Outcomes are log hospitalisation rates per 100,000 inhabitants (ATTs in log points; the \"% change\" rows and the text convert them to percentage changes); standard errors in parentheses, clustered at the MedStat region level; stars: *** p<0.01, ** p<0.05, * p<0.10.\n- `data/sources/arxiv-2606.14621v1.txt` — extract of Li, Pearson-Merkowitz & Yokum (2026), *Evaluating the Impact of Rhode Island's Self-Sustaining RESEA Program on Employment Outcomes*, arXiv:2606.14621v1 [econ.GN], CC BY 4.0: abstract, Section 3 Results (Table 2 with group means, treatment–control differences and ATE estimates with p-values and 95% CIs; results text; Section 3.1) and Table 3. Tables 2 and 3 were re-set one row per outcome (values verbatim; see the extract header).\n- `data/README.md` — provenance, retrieval times, licences, SHA-256 of the extracts.\n\n## Information-availability rules\n- The extracts are the only admissible evidence. Do not use remembered content of the papers, other versions, or outside knowledge of the programmes.\n- A percentage change implied by a log-point coefficient b is 100·(exp(b) − 1); a 95% confidence interval from a printed standard error is the estimate ± 1.96·SE (2.0 is also acceptable). Use these conventions when an assertion requires a conversion the source does not print.\n- \"Supported\" requires every element of the assertion to hold; an assertion that is partly correct and partly contradicted is `not_supported`. Use `not_assessable` only when the extract contains no quantity or comparison bearing on the claim (e.g. a subgroup the source never reports), not when the claim is merely imprecise.\n- A locator has the form `<source id> | Table <n> | row \"<row>\" | column \"<col>\"` or `<source id> | Section <n or title>`; one locator per assertion.\n\n## Required outputs\n- `out/results.json` with the keys:\n\n| key | type | unit | meaning |\n|---|---|---|---|\n| `verdicts` | object | — | {\"A1\": \"supported\" / \"not_supported\" / \"not_assessable\", …, \"A6\": …} |\n| `locators` | object | — | {\"A1\": \"<locator>\", …} — the table/section that decides the verdict (for `not_assessable`, the table/section where the relevant outcome is reported, or \"not reported in <source id>\") |\n| `reasons` | object | — | {\"A1\": \"<one sentence naming the decisive element>\", …} |\n| `n_supported`, `n_not_supported`, `n_not_assessable` | integer | — | counts over the six assertions |\n| `task_id` | string | — | \"F4-conf-02\" |\n| `feasibility` | string | — | \"complete\", \"partial\" or \"infeasible\" — refers to the task as a whole |\n| `feasibility_reason` | string or null | — | explanation if not complete |\n| `data_issues` | array of {\"issue\",\"handling\"} | — | problems detected in the inputs (rendering defects, internal inconsistencies of a source, etc.) and how they were handled; empty list if none |\n| `n_input_rows` | object | lines / items | {file name: number of lines} for every file under `data/` that you read (text files: number of newline-terminated lines as reported by `wc -l`; JSON files: number of top-level items) |\n| `n_analysed` | integer or null | — | number of reported items (values, assertions, effects or references) you actually assessed |\n| `random_seed` | integer or null | — | null (no randomness is involved) |\n\n- `out/report.md` with the sections: Question; Data and exclusions; Method; Results; Uncertainty; Limitations and open issues. \"Uncertainty\" must discuss which verdicts depend on a convention (critical value, log-to-percent conversion) and whether the verdict would change under a reasonable alternative.\n- `out/analysis.py` — running `~/wp29/venv/bin/python out/analysis.py` from the workspace root must regenerate `out/results.json` from `data/` only, deterministically (the script may encode the verdict logic explicitly; it must print the source lines it relies on).\n- `out/claims.json` — a list of the central claims of the report: [{\"id\": \"C1\", \"text\": \"...\", \"results_keys\": [\"...\"], \"status\": \"supported\"|\"unsupported\"|\"not_evaluated\", \"caveat\": \"...\"}].\n\n## Constraints\n- No network access. Python: `~/wp29/venv/bin/python` (numpy, pandas, scipy, statsmodels available; the standard library is sufficient for this task). Do not modify `data/`.\n- The source extracts under `data/sources/` are the **only** admissible evidence. Do not rely on memory of the papers or on other versions of them; if a quantity is not in the extract, it is not available.\n- Report numbers exactly as printed in the source (same sign, same number of decimals); do not round or rescale printed values unless the key definition asks for a transformation.\n- This task is designed to be completed in well under 20 minutes of work.\ntotal 32\ndrwxr-xr-x 6 simon-pierreboucher staff 192 oct. 29 23:45 .\ndrwxr-xr-x 161 simon-pierreboucher staff 5152 oct. 30 01:28 ..\n-rw-r--r-- 1 simon-pierreboucher staff 737 oct. 29 23:45 bundle.json\ndrwxr-xr-x 5 simon-pierreboucher staff 160 oct. 29 23:45 data\n-rw-r--r-- 1 simon-pierreboucher staff 1547 oct. 29 23:45 gate_spec.json\n-rw-r--r-- 1 simon-pierreboucher staff 6080 oct. 29 23:45 TASK.md\n\n./data:\ntotal 16\ndrwxr-xr-x 5 simon-pierreboucher staff 160 oct. 29 23:45 .\ndrwxr-xr-x 6 simon-pierreboucher staff 192 oct. 29 23:45 ..\n-rw-r--r-- 1 simon-pierreboucher staff 1365 oct. 29 23:45 assertions.json\n-rw-r--r-- 1 simon-pierreboucher staff 2017 oct. 29 23:45 README.md\ndrwxr-xr-x 4 simon-pierreboucher staff 128 oct. 29 23:45 sources\n\n./data/sources:\ntotal 64\ndrwxr-xr-x 4 simon-pierreboucher staff 128 oct. 29 23:45 .\ndrwxr-xr-x 5 simon-pierreboucher staff 160 oct. 29 23:45 ..\n-rw-r--r-- 1 simon-pierreboucher staff 13405 oct. 29 23:45 arxiv-2606.14621v1.txt\n-rw-r--r-- 1 simon-pierreboucher staff 12401 oct. 29 23:45 arxiv-2609.27732v1.txt","is_error":true,"tool_use_id":"toolu_01EW1CZGmqKJjsKX3h2R6DQb"}]},"uuid":"371e5cc8-d91e-4507-9e91-76467469c2ee","timestamp":"2026-10-30T05:29:03.292Z","toolUseResult":"Error: Exit code 1\n# F4-conf-02 — Is each quoted assertion supported by the source it cites?\n\n## Scientific question\nA literature review drafted from two open-access studies contains six assertions, each citing one of the two sources provided. For every assertion, decide from the cited extract alone whether it is **supported** (every element of the assertion — sign, magnitude, uncertainty statement, significance claim, population — is stated in, or follows arithmetically from, the source), **not_supported** (at least one element is contradicted by the source or does not follow from it), or **not_assessable** (the source does not report the quantity or comparison needed to judge the assertion, so it can be neither confirmed nor refuted from the extract). Each verdict must carry a locator (source id and the table, row/column or section that decides it) and a one-sentence reason. The estimands are the six verdicts.\n\n## Inputs\n- `data/assertions.json` — list of the six assertions: {\"id\", \"cites\" (source id), \"text\"}.\n- `data/sources/arxiv-2609.27732v1.txt` — extract of Armendariz (2026), *Do Drug Consumption Rooms Reduce Drug-Related Hospitalizations? Evidence from Switzerland*, arXiv:2609.27732v1 [econ.GN], CC BY 4.0: abstract, Section 6 (Results: Table 6 overall ATT by buffer; Table 7 ATT by outcome category and buffer; Section 6.1 Mechanisms) and Appendix Table A19. Outcomes are log hospitalisation rates per 100,000 inhabitants (ATTs in log points; the \"% change\" rows and the text convert them to percentage changes); standard errors in parentheses, clustered at the MedStat region level; stars: *** p<0.01, ** p<0.05, * p<0.10.\n- `data/sources/arxiv-2606.14621v1.txt` — extract of Li, Pearson-Merkowitz & Yokum (2026), *Evaluating the Impact of Rhode Island's Self-Sustaining RESEA Program on Employment Outcomes*, arXiv:2606.14621v1 [econ.GN], CC BY 4.0: abstract, Section 3 Results (Table 2 with group means, treatment–control differences and ATE estimates with p-values and 95% CIs; results text; Section 3.1) and Table 3. Tables 2 and 3 were re-set one row per outcome (values verbatim; see the extract header).\n- `data/README.md` — provenance, retrieval times, licences, SHA-256 of the extracts.\n\n## Information-availability rules\n- The extracts are the only admissible evidence. Do not use remembered content of the papers, other versions, or outside knowledge of the programmes.\n- A percentage change implied by a log-point coefficient b is 100·(exp(b) − 1); a 95% confidence interval from a printed standard error is the estimate ± 1.96·SE (2.0 is also acceptable). Use these conventions when an assertion requires a conversion the source does not print.\n- \"Supported\" requires every element of the assertion to hold; an assertion that is partly correct and partly contradicted is `not_supported`. Use `not_assessable` only when the extract contains no quantity or comparison bearing on the claim (e.g. a subgroup the source never reports), not when the claim is merely imprecise.\n- A locator has the form `<source id> | Table <n> | row \"<row>\" | column \"<col>\"` or `<source id> | Section <n or title>`; one locator per assertion.\n\n## Required outputs\n- `out/results.json` with the keys:\n\n| key | type | unit | meaning |\n|---|---|---|---|\n| `verdicts` | object | — | {\"A1\": \"supported\" / \"not_supported\" / \"not_assessable\", …, \"A6\": …} |\n| `locators` | object | — | {\"A1\": \"<locator>\", …} — the table/section that decides the verdict (for `not_assessable`, the table/section where the relevant outcome is reported, or \"not reported in <source id>\") |\n| `reasons` | object | — | {\"A1\": \"<one sentence naming the decisive element>\", …} |\n| `n_supported`, `n_not_supported`, `n_not_assessable` | integer | — | counts over the six assertions |\n| `task_id` | string | — | \"F4-conf-02\" |\n| `feasibility` | string | — | \"complete\", \"partial\" or \"infeasible\" — refers to the task as a whole |\n| `feasibility_reason` | string or null | — | explanation if not complete |\n| `data_issues` | array of {\"issue\",\"handling\"} | — | problems detected in the inputs (rendering defects, internal inconsistencies of a source, etc.) and how they were handled; empty list if none |\n| `n_input_rows` | object | lines / items | {file name: number of lines} for every file under `data/` that you read (text files: number of newline-terminated lines as reported by `wc -l`; JSON files: number of top-level items) |\n| `n_analysed` | integer or null | — | number of reported items (values, assertions, effects or references) you actually assessed |\n| `random_seed` | integer or null | — | null (no randomness is involved) |\n\n- `out/report.md` with the sections: Question; Data and exclusions; Method; Results; Uncertainty; Limitations and open issues. \"Uncertainty\" must discuss which verdicts depend on a convention (critical value, log-to-percent conversion) and whether the verdict would change under a reasonable alternative.\n- `out/analysis.py` — running `~/wp29/venv/bin/python out/analysis.py` from the workspace root must regenerate `out/results.json` from `data/` only, deterministically (the script may encode the verdict logic explicitly; it must print the source lines it relies on).\n- `out/claims.json` — a list of the central claims of the report: [{\"id\": \"C1\", \"text\": \"...\", \"results_keys\": [\"...\"], \"status\": \"supported\"|\"unsupported\"|\"not_evaluated\", \"caveat\": \"...\"}].\n\n## Constraints\n- No network access. Python: `~/wp29/venv/bin/python` (numpy, pandas, scipy, statsmodels available; the standard library is sufficient for this task). Do not modify `data/`.\n- The source extracts under `data/sources/` are the **only** admissible evidence. Do not rely on memory of the papers or on other versions of them; if a quantity is not in the extract, it is not available.\n- Report numbers exactly as printed in the source (same sign, same number of decimals); do not round or rescale printed values unless the key definition asks for a transformation.\n- This task is designed to be completed in well under 20 minutes of work.\ntotal 32\ndrwxr-xr-x 6 simon-pierreboucher staff 192 oct. 29 23:45 .\ndrwxr-xr-x 161 simon-pierreboucher staff 5152 oct. 30 01:28 ..\n-rw-r--r-- 1 simon-pierreboucher staff 737 oct. 29 23:45 bundle.json\ndrwxr-xr-x 5 simon-pierreboucher staff 160 oct. 29 23:45 data\n-rw-r--r-- 1 simon-pierreboucher staff 1547 oct. 29 23:45 gate_spec.json\n-rw-r--r-- 1 simon-pierreboucher staff 6080 oct. 29 23:45 TASK.md\n\n./data:\ntotal 16\ndrwxr-xr-x 5 simon-pierreboucher staff 160 oct. 29 23:45 .\ndrwxr-xr-x 6 simon-pierreboucher staff 192 oct. 29 23:45 ..\n-rw-r--r-- 1 simon-pierreboucher staff 1365 oct. 29 23:45 assertions.json\n-rw-r--r-- 1 simon-pierreboucher staff 2017 oct. 29 23:45 README.md\ndrwxr-xr-x 4 simon-pierreboucher staff 128 oct. 29 23:45 sources\n\n./data/sources:\ntotal 64\ndrwxr-xr-x 4 simon-pierreboucher staff 128 oct. 29 23:45 .\ndrwxr-xr-x 5 simon-pierreboucher staff 160 oct. 29 23:45 ..\n-rw-r--r-- 1 simon-pierreboucher staff 13405 oct. 29 23:45 arxiv-2606.14621v1.txt\n-rw-r--r-- 1 simon-pierreboucher staff 12401 oct. 29 23:45 arxiv-2609.27732v1.txt","sandboxed":false,"sourceToolAssistantUUID":"4b84c5a5-e2f9-4881-83ed-90ffe45fa214","permissionDecision":{"decision":"accept","source":"config","reasonType":"rule","ruleSource":"cliArg"},"userType":"external","entrypoint":"sdk-cli","cwd":"/Users/simon-pierreboucher/wp29/runs/RC0094","sessionId":"989b99df-8772-4c22-b5b4-b743dc4be974","version":"2.1.314","gitBranch":"HEAD"}15{"type":"api-request-blob","sessionId":"989b99df-8772-4c22-b5b4-b743dc4be974","hash":"0d143f4a727ad23d22d04436896b94a209fdcd5ccedd740b3dac7ed86641d248","message":{"role":"assistant","content":[{"type":"thinking","thinking":"","signature":"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"},{"type":"tool_use","id":"toolu_01EW1CZGmqKJjsKX3h2R6DQb","name":"Bash","input":{"command":"cat TASK.md; 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wc -l data/README.md data/sources/*; shasum -a 256 data/*.json data/*.md data/sources/*","description":"Read inputs and metadata"},"caller":{"type":"direct"}}],"container":null,"stop_reason":"tool_use","stop_sequence":null,"stop_details":null,"usage":{"input_tokens":2,"cache_creation_input_tokens":3025,"cache_read_input_tokens":4315,"output_tokens":333,"output_tokens_details":{"thinking_tokens":0},"server_tool_use":{"web_search_requests":0,"web_fetch_requests":0},"service_tier":"standard","cache_creation":{"ephemeral_1h_input_tokens":0,"ephemeral_5m_input_tokens":3025},"inference_geo":"global","iterations":[],"speed":"standard","fallback_credit":null},"input_transformations":[],"diagnostics":null,"context_management":null},"apiBlockIndex":0,"requestId":"req_011CgXsS3gDXw7npnT1sionF","requestRef":"c03fa4b3-5aba-43e4-b8f8-419f1b7418ba","requestedModel":"claude-opus-5-5","type":"assistant","uuid":"13d4b4af-2dcc-43f1-80a0-2e350611f2ce","timestamp":"2026-10-30T05:29:04.863Z","effort":"medium","perTurnEffort":"medium","userType":"external","entrypoint":"sdk-cli","cwd":"/Users/simon-pierreboucher/wp29/runs/RC0094","sessionId":"989b99df-8772-4c22-b5b4-b743dc4be974","version":"2.1.314","gitBranch":"HEAD"}20{"parentUuid":"13d4b4af-2dcc-43f1-80a0-2e350611f2ce","isSidechain":false,"promptId":"9ebd33b9-1875-4076-855f-328e8dae8857","type":"user","message":{"role":"user","content":[{"tool_use_id":"toolu_01J56nJbEHVuqSoTGr8ab75N","type":"tool_result","content":"[\n {\n \"id\": \"A1\",\n \"cites\": \"arxiv-2609.27732v1\",\n \"text\": \"Within 5 km of a drug consumption room, the overall ATT on the log drug-related hospitalisation rate is −0.431 (SE 0.210), statistically significant at the 5% level, which corresponds to a 35.0% reduction in the hospitalisation rate.\"\n },\n {\n \"id\": \"A2\",\n \"cites\": \"arxiv-2609.27732v1\",\n \"text\": \"At the 1 km buffer, the estimated ATT for HIV hospitalisations is negative (−0.063), i.e. HIV hospitalisations fall after a DCR opening in the immediate vicinity.\"\n },\n {\n \"id\": \"A3\",\n \"cites\": \"arxiv-2609.27732v1\",\n \"text\": \"The 3 km ATT of −0.283 implies a 28.3% reduction in drug-related hospitalisations within 3 km of a DCR.\"\n },\n {\n \"id\": \"A4\",\n \"cites\": \"arxiv-2609.27732v1\",\n \"text\": \"For viral hepatitis at the 5 km buffer, the 95% confidence interval of the ATT is approximately [−0.66, −0.16] and therefore excludes zero.\"\n },\n {\n \"id\": \"A5\",\n \"cites\": \"arxiv-2609.27732v1\",\n \"text\": \"The reduction in drug-related hospitalisations after a DCR opening is larger for men than for women.\"\n },\n {\n \"id\": \"A6\",\n \"cites\": \"arxiv-2606.14621v1\",\n \"text\": \"Selection into RESEA reduced the number of weeks on UI by 1.99 weeks (95% CI [−2.24, −1.75]), an 11.5% decrease relative to the control-group mean of 17.3 weeks.\"\n }\n]\n# Data provenance — F4-conf-02\n\nAll files under `data/sources/` are plain-text extracts of publicly accessible documents, prepared by the task designer on 2026-10-30 (UTC). Each extract begins with a provenance header (title, authors, bibliographic record, retrieval URL and UTC, SHA-256 of the retrieved HTML, license, list of included and omitted sections). Only the excerpts needed for the task are reproduced; everything else is omitted. Tables are rendered one row per line with ` | ` between cells; in regression tables, the line following a coefficient row holds the standard errors in parentheses as printed in the original.\n\n| file | document | retrieval UTC | license | SHA-256 of the extract |\n|---|---|---|---|---|\n| `sources/arxiv-2609.27732v1.txt` | Armendariz, A. (2026). Do Drug Consumption Rooms Reduce Drug-Related Hospitalizations? Evidence from Switzerland. arXiv:2609.27732v1 [econ.GN]. https://arxiv.org/abs/2609.27732v1 (full text: https://arxiv.org/html/2609.27732v1) | 2026-10-30T03:23:18Z | CC BY 4.0 | ee2d444d2f78f2af2ca2cf69b59a61fcd7ac5e10ea29e8ddcd67917bf07d6a8b |\n| `sources/arxiv-2606.14621v1.txt` | Li, H. H., Pearson-Merkowitz, S., & Yokum, D. (2026). Evaluating the Impact of Rhode Island's Self-Sustaining Reemployment Services and Eligibility Assessment (RESEA) Program on Employment Outcomes. arXiv:2606.14621v1 [econ.GN]. https://arxiv.org/abs/2606.14621v1 (full text: https://arxiv.org/html/2606.14621v1) | 2026-10-30T03:23:18Z | CC BY 4.0 | 27c463c0a144d9d5a3916dc641f15b6029f6c68b5e574ad9074e7df1aeb0a238 |\n\nTask-specific input files (prepared by the task designer, not observed data):\n\n- `assertions.json` — the six assertions to be checked (id, cited source id, text), written by the task designer\n\nRights: arXiv e-prints are reproduced in part under the Creative Commons Attribution 4.0 licence shown on their arXiv abstract pages. No numbers were altered; where a table was re-set for legibility (RESEA Tables 2-3, London Table 3 header) the extract header says so.\n{\n \"task_id\": \"F4-conf-02\",\n \"required_files\": [\n \"out/results.json\",\n \"out/report.md\",\n \"out/analysis.py\",\n \"out/claims.json\"\n ],\n \"results_keys\": {\n \"verdicts\": {\n \"type\": \"object\",\n \"nullable\": false\n },\n \"locators\": {\n \"type\": \"object\",\n \"nullable\": false\n },\n \"reasons\": {\n \"type\": \"object\",\n \"nullable\": false\n },\n \"n_supported\": {\n \"type\": \"integer\",\n \"nullable\": false\n },\n \"n_not_supported\": {\n \"type\": \"integer\",\n \"nullable\": false\n },\n \"n_not_assessable\": {\n \"type\": \"integer\",\n \"nullable\": false\n },\n \"task_id\": {\n \"type\": \"string\",\n \"nullable\": false\n },\n \"feasibility\": {\n \"type\": \"string\",\n \"nullable\": false\n },\n \"feasibility_reason\": {\n \"type\": \"string\",\n \"nullable\": true\n },\n \"data_issues\": {\n \"type\": \"array\",\n \"nullable\": false\n },\n \"n_input_rows\": {\n \"type\": \"object\",\n \"nullable\": false\n },\n \"n_analysed\": {\n \"type\": \"integer\",\n \"nullable\": true\n },\n \"random_seed\": {\n \"type\": \"integer\",\n \"nullable\": true\n }\n },\n \"report_sections\": [\n \"Question\",\n \"Data and exclusions\",\n \"Method\",\n \"Results\",\n \"Uncertainty\",\n \"Limitations and open issues\"\n ],\n \"family_checks\": [\n \"claims_reference_existing_keys\",\n \"phase_ledger_consistent\"\n ],\n \"ci_pairs\": [],\n \"positive_keys\": [],\n \"chronology_pairs\": [],\n \"analysis_timeout_s\": 300,\n \"reproducibility_tolerance_rel\": 1e-06\n}\n{\n \"task_id\": \"F4-conf-02\",\n \"family\": \"F4\",\n \"split\": \"conf\",\n \"version\": \"1.0\",\n \"created_utc\": \"2026-10-30T03:45:06.399097+00:00\",\n \"files\": {\n \"TASK.md\": \"2f517ee00f69f6ba411c5189a9358a21afc763b36c88f8420603c079421a7c1a\",\n \"data/README.md\": \"5348bd49912099735108dbbe19ae09fa72bd600cb3d12b878658e6b9806198a7\",\n \"data/assertions.json\": \"2965ab3acc6f326653169b83a5345698b51fac88a556de65faf89210aea0cad4\",\n \"data/sources/arxiv-2606.14621v1.txt\": \"27c463c0a144d9d5a3916dc641f15b6029f6c68b5e574ad9074e7df1aeb0a238\",\n \"data/sources/arxiv-2609.27732v1.txt\": \"ee2d444d2f78f2af2ca2cf69b59a61fcd7ac5e10ea29e8ddcd67917bf07d6a8b\",\n \"gate_spec.json\": \"c7b67c16ad001e747b68be8a277a0e635f35013ccc3d44ef0f0a6270ec28991c\"\n }\n} 14 data/README.md\n 58 data/sources/arxiv-2606.14621v1.txt\n 134 data/sources/arxiv-2609.27732v1.txt\n 206 total\n2965ab3acc6f326653169b83a5345698b51fac88a556de65faf89210aea0cad4 data/assertions.json\n5348bd49912099735108dbbe19ae09fa72bd600cb3d12b878658e6b9806198a7 data/README.md\n27c463c0a144d9d5a3916dc641f15b6029f6c68b5e574ad9074e7df1aeb0a238 data/sources/arxiv-2606.14621v1.txt\nee2d444d2f78f2af2ca2cf69b59a61fcd7ac5e10ea29e8ddcd67917bf07d6a8b data/sources/arxiv-2609.27732v1.txt","is_error":false}]},"uuid":"41c78bd1-1d0b-4204-8f7a-d8666b5ea25b","timestamp":"2026-10-30T05:29:04.903Z","toolUseResult":{"stdout":"[\n {\n \"id\": \"A1\",\n \"cites\": \"arxiv-2609.27732v1\",\n \"text\": \"Within 5 km of a drug consumption room, the overall ATT on the log drug-related hospitalisation rate is −0.431 (SE 0.210), statistically significant at the 5% level, which corresponds to a 35.0% reduction in the hospitalisation rate.\"\n },\n {\n \"id\": \"A2\",\n \"cites\": \"arxiv-2609.27732v1\",\n \"text\": \"At the 1 km buffer, the estimated ATT for HIV hospitalisations is negative (−0.063), i.e. HIV hospitalisations fall after a DCR opening in the immediate vicinity.\"\n },\n {\n \"id\": \"A3\",\n \"cites\": \"arxiv-2609.27732v1\",\n \"text\": \"The 3 km ATT of −0.283 implies a 28.3% reduction in drug-related hospitalisations within 3 km of a DCR.\"\n },\n {\n \"id\": \"A4\",\n \"cites\": \"arxiv-2609.27732v1\",\n \"text\": \"For viral hepatitis at the 5 km buffer, the 95% confidence interval of the ATT is approximately [−0.66, −0.16] and therefore excludes zero.\"\n },\n {\n \"id\": \"A5\",\n \"cites\": \"arxiv-2609.27732v1\",\n \"text\": \"The reduction in drug-related hospitalisations after a DCR opening is larger for men than for women.\"\n },\n {\n \"id\": \"A6\",\n \"cites\": \"arxiv-2606.14621v1\",\n \"text\": \"Selection into RESEA reduced the number of weeks on UI by 1.99 weeks (95% CI [−2.24, −1.75]), an 11.5% decrease relative to the control-group mean of 17.3 weeks.\"\n }\n]\n# Data provenance — F4-conf-02\n\nAll files under `data/sources/` are plain-text extracts of publicly accessible documents, prepared by the task designer on 2026-10-30 (UTC). Each extract begins with a provenance header (title, authors, bibliographic record, retrieval URL and UTC, SHA-256 of the retrieved HTML, license, list of included and omitted sections). Only the excerpts needed for the task are reproduced; everything else is omitted. Tables are rendered one row per line with ` | ` between cells; in regression tables, the line following a coefficient row holds the standard errors in parentheses as printed in the original.\n\n| file | document | retrieval UTC | license | SHA-256 of the extract |\n|---|---|---|---|---|\n| `sources/arxiv-2609.27732v1.txt` | Armendariz, A. (2026). Do Drug Consumption Rooms Reduce Drug-Related Hospitalizations? Evidence from Switzerland. arXiv:2609.27732v1 [econ.GN]. https://arxiv.org/abs/2609.27732v1 (full text: https://arxiv.org/html/2609.27732v1) | 2026-10-30T03:23:18Z | CC BY 4.0 | ee2d444d2f78f2af2ca2cf69b59a61fcd7ac5e10ea29e8ddcd67917bf07d6a8b |\n| `sources/arxiv-2606.14621v1.txt` | Li, H. H., Pearson-Merkowitz, S., & Yokum, D. (2026). Evaluating the Impact of Rhode Island's Self-Sustaining Reemployment Services and Eligibility Assessment (RESEA) Program on Employment Outcomes. arXiv:2606.14621v1 [econ.GN]. https://arxiv.org/abs/2606.14621v1 (full text: https://arxiv.org/html/2606.14621v1) | 2026-10-30T03:23:18Z | CC BY 4.0 | 27c463c0a144d9d5a3916dc641f15b6029f6c68b5e574ad9074e7df1aeb0a238 |\n\nTask-specific input files (prepared by the task designer, not observed data):\n\n- `assertions.json` — the six assertions to be checked (id, cited source id, text), written by the task designer\n\nRights: arXiv e-prints are reproduced in part under the Creative Commons Attribution 4.0 licence shown on their arXiv abstract pages. 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1\tSOURCE EXTRACT — arxiv-2609.27732v1\n 2\tTitle: Do Drug Consumption Rooms Reduce Drug-Related Hospitalizations? Evidence from Switzerland\n 3\tAuthors: Ana Armendariz (University of St. Gallen)\n 4\tBibliographic record: arXiv:2609.27732v1 [econ.GN], submitted 23 Sep 2026 (version 1, the only version at retrieval). Abstract page: https://arxiv.org/abs/2609.27732v1\n 5\tRetrieved: https://arxiv.org/html/2609.27732v1 on 2026-10-30T03:23:18Z (SHA-256 of the retrieved HTML: 22b06050f4ff6e665aedd80561fa4031b1717867ecfeca71d1d2902ee1b09f52)\n 6\tLicense: CC BY 4.0 (license shown on the arXiv abstract page; https://creativecommons.org/licenses/by/4.0/). Reproduced in part with attribution.\n 7\tExtract contents: title, author, date and abstract; Section 6 'Results' in full (Figure notes, Table 6, Table 7, Section 6.1 'Mechanisms'); Appendix Table A19 with its note and the paragraph that discusses it.\n 8\tOmitted: Sections 1-5 and 7, the other appendix tables and figures, the references.\n 9\tRendering note: converted from the HTML rendering to plain text. Tables are rendered one row per line with \" | \" separating cells; in regression tables the line following a coefficient row holds the standard errors in parentheses, exactly as printed. Mathematical expressions appear as LaTeX source; non-breaking spaces were replaced by ordinary spaces. No numbers were altered.\n 10\t================================================================\n 11\t\n 12\t# Do Drug Consumption Rooms Reduce Drug-Related Hospitalizations? Evidence from Switzerland\n 13\t\n 14\tAna Armendariz*\n 15\t\n 16\tSeptember 23, 2026\n 17\t\n 18\tThis paper estimates the causal effect of drug consumption room (DCR) openings on drug-related hospitalizations in Switzerland. I exploit the staggered introduction of DCRs across Swiss cities between 1998 and 2022, using individual-level hospital records and a difference-in-differences estimator. DCR openings reduce drug-related hospitalization rates by roughly 35% within 5 km of a facility. The reduction is most pronounced for fatal outcomes, which fall by 35% while narcotics poisoning hospitalizations rise by a comparable amount, consistent with DCRs converting potentially fatal overdoses into non-fatal hospitalizations. Mental and behavioral disorder hospitalizations decline by 32% while estimates for Hepatitis and HIV are imprecise. The findings support the role of DCRs as an effective harm reduction strategy.\n 19\t\n 20\tKeywords: Drug Consumption Rooms, Harm Reduction, Hospitalizations, Drugs, Public Health, Causal Inference\n 21\t\n 22\t## 6 Results\n 23\t\n 24\tThis section reports the effect of DCR openings on the rate of drug-related hospitalizations per 100,000 inhabitants. I begin with the event-study estimates and then present the overall pooled ATT. I then disaggregate the overall outcome into its sub-outcome categories and report the same estimates for each.\n 25\t\n 26\tFigure 6: Event study estimates by buffer zone, \\pm 5-year window\n 27\t\n 28\tNote: The figure plots event-study coefficients from the doubly robust estimator of Callaway and Sant’Anna (2021) for regions within 5 km of a DCR opening. The comparison group consists of never-treated regions (608 control regions). The outcome is the log drug-related hospitalization rate per 100,000 inhabitants. The sample includes all staggered-treated MedStat regions within 5 km of a DCR that opened between 1998 and 2022 and all never-treated regions. The estimation uses a \\pm 5-year window relative to DCR opening, with t=-5 and t=+5 representing pooled endpoint bins that absorb all periods beyond the window. The reference period is a universal base period. Regions near DCRs that opened before 1998 (always-treated) are excluded through out. 95% confidence intervals are based on standard errors clustered at the MedStat region level. Results for the 1 km and 3 km buffer specifications are reported in Appendix Figure A17.\n 29\t\n 30\tFigure 6 presents the event study estimates for the 5 km buffer specifications. I focus on the 5 km buffer specification, as it includes the largest number of treated regions and yields the most precise estimates. I summarize dynamic effects over a symmetric five year window around DCR openings. This window avoids relying on distant leads and lags that are informed by only a small subset of adopters. Pre-treatment coefficients are small and statistically insignificant, supporting the parallel trends assumption. The post-treatment coefficients are consistently negative, indicating a reduction in drug-related hospitalizations following DCR openings. The estimates of the overall summary of ATTs based on calendar time aggregation of Callaway and Sant’Anna (2021) is around -35% reduction in hospitalizations due to drugs.\n 31\t\n 32\tTable 6: Overall Average Treatment Effect on the Treated (ATT)\n 33\t\n 34\t| 1 km | 3 km | 5 km\n 35\t\n 36\tATT | -0.399 | -0.283 | -0.431**\n 37\t\n 38\t| (0.412) | (0.279) | (0.210)\n 39\t\n 40\t% change | -32.9% | -24.7% | -35.0%\n 41\t\n 42\tTreated regions | 7 | 35 | 50\n 43\t\n 44\tControl regions | 608 | 608 | 608\n 45\t\n 46\tObservations | 16,175 | 16,875 | 17,250\n 47\t\n 48\tNote: The table reports the overall ATT estimated using the doubly robust Callaway and Sant’Anna (2021) estimator with never-treated controls and a universal base period. The outcome is the log drug-related hospitalization rate per 100,000 inhabitants. Columns differ in the geographic buffer used to define treated Medstat regions. The control group consists of 608 never-treated Medstat regions\n 49\tthroughout. Regions near DCRs that opened before 1998\n 50\t(always-treated) are excluded. Standard errors clustered at the Medstat region level in\n 51\tparentheses. Significance: {}^{***}p<0.01 , {}^{**}p<0.05 ,\n 52\t{}^{*}p<0.10 .\n 53\t\n 54\tTable 6 reports the pooled ATT for the 1 km, 3 km and 5 km buffer specification, aggregating the dynamic treatment effects into a single estimate averaged across all post-treatment periods and cohorts. The 5 km specification, yields an ATT of -0.431\n 55\tcorresponding to a 35% reduction in the drug-related hospitalization rate. This estimate is statistically significant at the 5% level. The 3 km and 1 km estimates point in the same direction but are less precise, due to the smaller number of treated regions.\n 56\t\n 57\tTo further explore the mechanisms through which DCR openings affect drug-related hospitalizations, I disaggregate the main outcome into five diagnostic\n 58\tsub-categories: (i) mental and behavioral disorders due to psychoactive substance use, (ii) viral hepatitis, (iii) HIV, (iv) poisoning by narcotics and psychodysleptics, and (v) fatal drug-related hospitalizations. Accidental poisoning is excluded due to the very small number of cases.\n 59\t\n 60\tFigure 7: Event study: Sub-outcome estimates,\n 61\twithin 5 km, \\pm 5-year window\n 62\t\n 63\tNote: The figure plots event-study coefficients from the doubly robust Callaway & Sant’Anna (2021) estimator for four diagnostic sub-categories of drug-related hospitalizations. Each panel uses a separate y -axis to accommodate differences in scale across outcomes. The sample includes all staggered-treated MedStat regions within 5 km of a\n 64\tDCR that opened between 1998 and 2022. The reference period is a universal base period. Regions near DCRs that opened before 1998 (always-treated) are excluded. 95% confidence intervals are based on standard errors clustered at the MedStat region level.\n 65\t\n 66\tTable 7: Overall ATT by Outcome Category and Buffer Zone\n 67\t\n 68\tOutcome | 1 km | 3 km | 5 km\n 69\t\n 70\tMental/Behavioral | -0.354 | -0.202 | -0.381*\n 71\t\n 72\t| (0.382) | (0.244) | (0.220)\n 73\t\n 74\tHepatitis | -0.270 | -0.413 | -0.406\n 75\t\n 76\t| (0.486) | (0.270) | (0.250)\n 77\t\n 78\tHIV | 0.063 | -0.239 | -0.340\n 79\t\n 80\t| (0.801) | (0.337) | (0.294)\n 81\t\n 82\tNarcotics | 1.186*** | 0.549*** | 0.390**\n 83\t\n 84\t| (0.288) | (0.187) | (0.165)\n 85\t\n 86\tDrug-related (fatal) | -1.207*** | -0.290 | -0.354**\n 87\t\n 88\t| (0.137) | (0.215) | (0.178)\n 89\t\n 90\tTreated regions | 7 | 35 | 50\n 91\t\n 92\tControl regions | 608 (never-treated) | |\n 93\t\n 94\tNote: Each cell reports the overall ATT from\n 95\tthe doubly robust Callaway & Sant’Anna (2021) estimator with\n 96\tnever-treated controls and a universal base period. Outcomes are\n 97\tlog hospitalization rates per 100,000 inhabitants. Sub-outcomes:\n 98\tmental and behavioral disorders (F11–F19), viral hepatitis (B15–B19),\n 99\tHIV disease (B20–B24), narcotics/psychodysleptics (T40). The 1 km\n 100\testimates are identified from a single treated region per cohort and\n 101\tshould be interpreted with caution. Regions near DCRs opened before\n 102\t1998 excluded. Standard errors clustered at the Medstat region level.\n 103\tSignificance: {}^{***}p<0.01 , {}^{**}p<0.05 , {}^{*}p<0.10 .\n 104\t\n 105\tFigure 7 and Table 7 repeat the estimation for the five diagnostic categories. From Table 7, the ATT estimates for hospitalizations due to mental and behavioral disorders are consistently negative and marginally significant at the 5 km buffer specification. Moreover, the estimates of hepatitis are also negative and of comparable magnitude but insignificant. However, the event-study path in Figure 7 shows a gradual decline that builds from year 3 onward, consistent with a slow-acting reduction in needle sharing. HIV estimates are insignificant and close to zero. Narcotics poisoning hospitalizations rise after DCR opening and remain positive across all buffers. Lastly, fatal drug-related hospitalizations move in the opposite direction, falling after opening the DCR. The opposing patterns in narcotics and fatal hospitalizations suggest that DCRs convert events that would otherwise be fatal into survivable hospital contacts.\n 106\t\n 107\t### 6.1 Mechanisms\n 108\t\n 109\tThe sub-outcome results point to two channels through which DCRs reduce drug-related hospitalizations. The first is overdose supervision. DCRs provide a medically supervised environment where staff can control the dose consumed, perform resuscitation, and call emergency services when an overdose occurs. When supervision prevents a death that would otherwise happen outside a hospital, the consequence is a simultaneous decline in fatal drug-related hospitalizations and a rise in non-fatal poisoning contacts, as events that would have ended in death instead end in a hospital visit. The results are consistent with this prediction. Drug-related fatal hospitalizations fall near DCRs, by approximately 30% at 5 km, while narcotics and psychodysleptics hospitalizations rise by 47% at 5 km. The opposing signs and spatial concentration of these two effects are consistent with a\n 110\tsubstitution from out-of-hospital mortality to in-hospital survival. Since I cannot observe overdose events that do not result in a hospital contact, this interpretation is suggestive rather than identified, but it is consistent with the clinical evidence on DCR-based overdose reversals\n 111\t(Kerr et al., 2017; Hedrich, 2004).\n 112\t\n 113\tThe second channel is harm reduction for blood-borne diseases. DCRs distribute sterile injection equipment, which reduces needle sharing and the transmission of viral hepatitis and HIV. Unlike overdose prevention, these effects are expected to emerge slowly, since disease progression and hospitalization take years to follow from initial infection. The event-study path for hepatitis is consistent with this lag. The estimates are close to zero in the first two post-treatment years and become progressively more negative from year 3 onward, reaching approximately 40% below baseline by year 5. HIV estimates are near zero through out the analysis, with wide confidence intervals. A longer panel and additional out-patient data would be needed to determine whether these trends continue and to get more precise estimates.\n 114\t\n 115\tA third potential channel is referral to treatment and social services. DCRs routinely connect users to addiction treatment, primary care, and housing support, and a sustained reduction in hospitalizations could partly reflect better long-term management of drug dependence. The regional hospitalization panel used in this paper does not contain information on treatment entry or service use, so I cannot separate this channel from the two described above. It remains a plausible additional mechanism that future work with information on treatment take up data could examine.\n 116\t\n 117\tTable A19: Robustness: Overall ATT Across Estimators — 5 km buffer, \\pm 5-year window\n 118\t\n 119\t| CS-DR | Sun & Abraham | Synthetic DiD | Stacked DiD\n 120\t\n 121\tATT | -0.431** | -0.438** | -0.362* | -0.149***\n 122\t\n 123\t| (0.218) | (0.208) | (0.205) | (0.038)\n 124\t\n 125\t% change | -35.0% | -35.5% | -30.3% | -13.9%\n 126\t\n 127\tTreated regions | 50 | | |\n 128\t\n 129\tControl regions | 608 | | |\n 130\t\n 131\tObservations | 17,250 | | |\n 132\t\n 133\tNote: All specifications use the 5 km buffer,\n 134\tnever-treated comparison regions (640 regions), and a \\pm 5-year window","is_error":false}]},"uuid":"cadd5626-64cb-4236-8cb9-72d457afd0c9","timestamp":"2026-10-30T05:29:05.540Z","toolUseResult":{"stdout":" 1\tSOURCE EXTRACT — arxiv-2609.27732v1\n 2\tTitle: Do Drug Consumption Rooms Reduce Drug-Related Hospitalizations? Evidence from Switzerland\n 3\tAuthors: Ana Armendariz (University of St. Gallen)\n 4\tBibliographic record: arXiv:2609.27732v1 [econ.GN], submitted 23 Sep 2026 (version 1, the only version at retrieval). Abstract page: https://arxiv.org/abs/2609.27732v1\n 5\tRetrieved: https://arxiv.org/html/2609.27732v1 on 2026-10-30T03:23:18Z (SHA-256 of the retrieved HTML: 22b06050f4ff6e665aedd80561fa4031b1717867ecfeca71d1d2902ee1b09f52)\n 6\tLicense: CC BY 4.0 (license shown on the arXiv abstract page; https://creativecommons.org/licenses/by/4.0/). Reproduced in part with attribution.\n 7\tExtract contents: title, author, date and abstract; Section 6 'Results' in full (Figure notes, Table 6, Table 7, Section 6.1 'Mechanisms'); Appendix Table A19 with its note and the paragraph that discusses it.\n 8\tOmitted: Sections 1-5 and 7, the other appendix tables and figures, the references.\n 9\tRendering note: converted from the HTML rendering to plain text. Tables are rendered one row per line with \" | \" separating cells; in regression tables the line following a coefficient row holds the standard errors in parentheses, exactly as printed. Mathematical expressions appear as LaTeX source; non-breaking spaces were replaced by ordinary spaces. No numbers were altered.\n 10\t================================================================\n 11\t\n 12\t# Do Drug Consumption Rooms Reduce Drug-Related Hospitalizations? Evidence from Switzerland\n 13\t\n 14\tAna Armendariz*\n 15\t\n 16\tSeptember 23, 2026\n 17\t\n 18\tThis paper estimates the causal effect of drug consumption room (DCR) openings on drug-related hospitalizations in Switzerland. I exploit the staggered introduction of DCRs across Swiss cities between 1998 and 2022, using individual-level hospital records and a difference-in-differences estimator. DCR openings reduce drug-related hospitalization rates by roughly 35% within 5 km of a facility. The reduction is most pronounced for fatal outcomes, which fall by 35% while narcotics poisoning hospitalizations rise by a comparable amount, consistent with DCRs converting potentially fatal overdoses into non-fatal hospitalizations. Mental and behavioral disorder hospitalizations decline by 32% while estimates for Hepatitis and HIV are imprecise. The findings support the role of DCRs as an effective harm reduction strategy.\n 19\t\n 20\tKeywords: Drug Consumption Rooms, Harm Reduction, Hospitalizations, Drugs, Public Health, Causal Inference\n 21\t\n 22\t## 6 Results\n 23\t\n 24\tThis section reports the effect of DCR openings on the rate of drug-related hospitalizations per 100,000 inhabitants. I begin with the event-study estimates and then present the overall pooled ATT. I then disaggregate the overall outcome into its sub-outcome categories and report the same estimates for each.\n 25\t\n 26\tFigure 6: Event study estimates by buffer zone, \\pm 5-year window\n 27\t\n 28\tNote: The figure plots event-study coefficients from the doubly robust estimator of Callaway and Sant’Anna (2021) for regions within 5 km of a DCR opening. The comparison group consists of never-treated regions (608 control regions). The outcome is the log drug-related hospitalization rate per 100,000 inhabitants. The sample includes all staggered-treated MedStat regions within 5 km of a DCR that opened between 1998 and 2022 and all never-treated regions. The estimation uses a \\pm 5-year window relative to DCR opening, with t=-5 and t=+5 representing pooled endpoint bins that absorb all periods beyond the window. The reference period is a universal base period. Regions near DCRs that opened before 1998 (always-treated) are excluded through out. 95% confidence intervals are based on standard errors clustered at the MedStat region level. Results for the 1 km and 3 km buffer specifications are reported in Appendix Figure A17.\n 29\t\n 30\tFigure 6 presents the event study estimates for the 5 km buffer specifications. I focus on the 5 km buffer specification, as it includes the largest number of treated regions and yields the most precise estimates. I summarize dynamic effects over a symmetric five year window around DCR openings. This window avoids relying on distant leads and lags that are informed by only a small subset of adopters. Pre-treatment coefficients are small and statistically insignificant, supporting the parallel trends assumption. The post-treatment coefficients are consistently negative, indicating a reduction in drug-related hospitalizations following DCR openings. The estimates of the overall summary of ATTs based on calendar time aggregation of Callaway and Sant’Anna (2021) is around -35% reduction in hospitalizations due to drugs.\n 31\t\n 32\tTable 6: Overall Average Treatment Effect on the Treated (ATT)\n 33\t\n 34\t| 1 km | 3 km | 5 km\n 35\t\n 36\tATT | -0.399 | -0.283 | -0.431**\n 37\t\n 38\t| (0.412) | (0.279) | (0.210)\n 39\t\n 40\t% change | -32.9% | -24.7% | -35.0%\n 41\t\n 42\tTreated regions | 7 | 35 | 50\n 43\t\n 44\tControl regions | 608 | 608 | 608\n 45\t\n 46\tObservations | 16,175 | 16,875 | 17,250\n 47\t\n 48\tNote: The table reports the overall ATT estimated using the doubly robust Callaway and Sant’Anna (2021) estimator with never-treated controls and a universal base period. The outcome is the log drug-related hospitalization rate per 100,000 inhabitants. Columns differ in the geographic buffer used to define treated Medstat regions. The control group consists of 608 never-treated Medstat regions\n 49\tthroughout. Regions near DCRs that opened before 1998\n 50\t(always-treated) are excluded. Standard errors clustered at the Medstat region level in\n 51\tparentheses. Significance: {}^{***}p<0.01 , {}^{**}p<0.05 ,\n 52\t{}^{*}p<0.10 .\n 53\t\n 54\tTable 6 reports the pooled ATT for the 1 km, 3 km and 5 km buffer specification, aggregating the dynamic treatment effects into a single estimate averaged across all post-treatment periods and cohorts. The 5 km specification, yields an ATT of -0.431\n 55\tcorresponding to a 35% reduction in the drug-related hospitalization rate. This estimate is statistically significant at the 5% level. The 3 km and 1 km estimates point in the same direction but are less precise, due to the smaller number of treated regions.\n 56\t\n 57\tTo further explore the mechanisms through which DCR openings affect drug-related hospitalizations, I disaggregate the main outcome into five diagnostic\n 58\tsub-categories: (i) mental and behavioral disorders due to psychoactive substance use, (ii) viral hepatitis, (iii) HIV, (iv) poisoning by narcotics and psychodysleptics, and (v) fatal drug-related hospitalizations. Accidental poisoning is excluded due to the very small number of cases.\n 59\t\n 60\tFigure 7: Event study: Sub-outcome estimates,\n 61\twithin 5 km, \\pm 5-year window\n 62\t\n 63\tNote: The figure plots event-study coefficients from the doubly robust Callaway & Sant’Anna (2021) estimator for four diagnostic sub-categories of drug-related hospitalizations. Each panel uses a separate y -axis to accommodate differences in scale across outcomes. The sample includes all staggered-treated MedStat regions within 5 km of a\n 64\tDCR that opened between 1998 and 2022. The reference period is a universal base period. Regions near DCRs that opened before 1998 (always-treated) are excluded. 95% confidence intervals are based on standard errors clustered at the MedStat region level.\n 65\t\n 66\tTable 7: Overall ATT by Outcome Category and Buffer Zone\n 67\t\n 68\tOutcome | 1 km | 3 km | 5 km\n 69\t\n 70\tMental/Behavioral | -0.354 | -0.202 | -0.381*\n 71\t\n 72\t| (0.382) | (0.244) | (0.220)\n 73\t\n 74\tHepatitis | -0.270 | -0.413 | -0.406\n 75\t\n 76\t| (0.486) | (0.270) | (0.250)\n 77\t\n 78\tHIV | 0.063 | -0.239 | -0.340\n 79\t\n 80\t| (0.801) | (0.337) | (0.294)\n 81\t\n 82\tNarcotics | 1.186*** | 0.549*** | 0.390**\n 83\t\n 84\t| (0.288) | (0.187) | (0.165)\n 85\t\n 86\tDrug-related (fatal) | -1.207*** | -0.290 | -0.354**\n 87\t\n 88\t| (0.137) | (0.215) | (0.178)\n 89\t\n 90\tTreated regions | 7 | 35 | 50\n 91\t\n 92\tControl regions | 608 (never-treated) | |\n 93\t\n 94\tNote: Each cell reports the overall ATT from\n 95\tthe doubly robust Callaway & Sant’Anna (2021) estimator with\n 96\tnever-treated controls and a universal base period. Outcomes are\n 97\tlog hospitalization rates per 100,000 inhabitants. Sub-outcomes:\n 98\tmental and behavioral disorders (F11–F19), viral hepatitis (B15–B19),\n 99\tHIV disease (B20–B24), narcotics/psychodysleptics (T40). The 1 km\n 100\testimates are identified from a single treated region per cohort and\n 101\tshould be interpreted with caution. Regions near DCRs opened before\n 102\t1998 excluded. Standard errors clustered at the Medstat region level.\n 103\tSignificance: {}^{***}p<0.01 , {}^{**}p<0.05 , {}^{*}p<0.10 .\n 104\t\n 105\tFigure 7 and Table 7 repeat the estimation for the five diagnostic categories. From Table 7, the ATT estimates for hospitalizations due to mental and behavioral disorders are consistently negative and marginally significant at the 5 km buffer specification. Moreover, the estimates of hepatitis are also negative and of comparable magnitude but insignificant. However, the event-study path in Figure 7 shows a gradual decline that builds from year 3 onward, consistent with a slow-acting reduction in needle sharing. HIV estimates are insignificant and close to zero. Narcotics poisoning hospitalizations rise after DCR opening and remain positive across all buffers. Lastly, fatal drug-related hospitalizations move in the opposite direction, falling after opening the DCR. The opposing patterns in narcotics and fatal hospitalizations suggest that DCRs convert events that would otherwise be fatal into survivable hospital contacts.\n 106\t\n 107\t### 6.1 Mechanisms\n 108\t\n 109\tThe sub-outcome results point to two channels through which DCRs reduce drug-related hospitalizations. The first is overdose supervision. DCRs provide a medically supervised environment where staff can control the dose consumed, perform resuscitation, and call emergency services when an overdose occurs. When supervision prevents a death that would otherwise happen outside a hospital, the consequence is a simultaneous decline in fatal drug-related hospitalizations and a rise in non-fatal poisoning contacts, as events that would have ended in death instead end in a hospital visit. The results are consistent with this prediction. Drug-related fatal hospitalizations fall near DCRs, by approximately 30% at 5 km, while narcotics and psychodysleptics hospitalizations rise by 47% at 5 km. The opposing signs and spatial concentration of these two effects are consistent with a\n 110\tsubstitution from out-of-hospital mortality to in-hospital survival. Since I cannot observe overdose events that do not result in a hospital contact, this interpretation is suggestive rather than identified, but it is consistent with the clinical evidence on DCR-based overdose reversals\n 111\t(Kerr et al., 2017; Hedrich, 2004).\n 112\t\n 113\tThe second channel is harm reduction for blood-borne diseases. DCRs distribute sterile injection equipment, which reduces needle sharing and the transmission of viral hepatitis and HIV. Unlike overdose prevention, these effects are expected to emerge slowly, since disease progression and hospitalization take years to follow from initial infection. The event-study path for hepatitis is consistent with this lag. The estimates are close to zero in the first two post-treatment years and become progressively more negative from year 3 onward, reaching approximately 40% below baseline by year 5. HIV estimates are near zero through out the analysis, with wide confidence intervals. A longer panel and additional out-patient data would be needed to determine whether these trends continue and to get more precise estimates.\n 114\t\n 115\tA third potential channel is referral to treatment and social services. DCRs routinely connect users to addiction treatment, primary care, and housing support, and a sustained reduction in hospitalizations could partly reflect better long-term management of drug dependence. The regional hospitalization panel used in this paper does not contain information on treatment entry or service use, so I cannot separate this channel from the two described above. It remains a plausible additional mechanism that future work with information on treatment take up data could examine.\n 116\t\n 117\tTable A19: Robustness: Overall ATT Across Estimators — 5 km buffer, \\pm 5-year window\n 118\t\n 119\t| CS-DR | Sun & Abraham | Synthetic DiD | Stacked DiD\n 120\t\n 121\tATT | -0.431** | -0.438** | -0.362* | -0.149***\n 122\t\n 123\t| (0.218) | (0.208) | (0.205) | (0.038)\n 124\t\n 125\t% change | -35.0% | -35.5% | -30.3% | -13.9%\n 126\t\n 127\tTreated regions | 50 | | |\n 128\t\n 129\tControl regions | 608 | | |\n 130\t\n 131\tObservations | 17,250 | | |\n 132\t\n 133\tNote: All specifications use the 5 km buffer,\n 134\tnever-treated comparison regions (640 regions), and a \\pm 5-year window","stderr":"","interrupted":false,"isImage":false,"noOutputExpected":false},"sandboxed":false,"sourceToolAssistantUUID":"92e11c24-28d4-464d-9068-fb94c3bcf05c","permissionDecision":{"decision":"accept","source":"config","reasonType":"rule","ruleSource":"cliArg"},"userType":"external","entrypoint":"sdk-cli","cwd":"/Users/simon-pierreboucher/wp29/runs/RC0094","sessionId":"989b99df-8772-4c22-b5b4-b743dc4be974","version":"2.1.314","gitBranch":"HEAD"}23{"parentUuid":"cadd5626-64cb-4236-8cb9-72d457afd0c9","isSidechain":false,"message":{"model":"claude-opus-5-5","id":"msg_011CgXsS3wacHwYxEDU9vdEV","type":"message","role":"assistant","content":[{"type":"tool_use","id":"toolu_017tEkcJ9kzZey79YCMckaFc","name":"Bash","input":{"command":"cat -n data/sources/arxiv-2606.14621v1.txt","description":"Read RESEA source"},"caller":{"type":"direct"}}],"container":null,"stop_reason":"tool_use","stop_sequence":null,"stop_details":null,"usage":{"input_tokens":2,"cache_creation_input_tokens":3025,"cache_read_input_tokens":4315,"output_tokens":333,"output_tokens_details":{"thinking_tokens":0},"server_tool_use":{"web_search_requests":0,"web_fetch_requests":0},"service_tier":"standard","cache_creation":{"ephemeral_1h_input_tokens":0,"ephemeral_5m_input_tokens":3025},"inference_geo":"global","iterations":[],"speed":"standard","fallback_credit":null},"input_transformations":[],"diagnostics":null,"context_management":null},"apiBlockIndex":2,"requestId":"req_011CgXsS3gDXw7npnT1sionF","requestRef":"c03fa4b3-5aba-43e4-b8f8-419f1b7418ba","requestedModel":"claude-opus-5-5","type":"assistant","uuid":"494c9db0-a116-4251-b8ac-30751a0f0a0e","timestamp":"2026-10-30T05:29:06.003Z","effort":"medium","perTurnEffort":"medium","userType":"external","entrypoint":"sdk-cli","cwd":"/Users/simon-pierreboucher/wp29/runs/RC0094","sessionId":"989b99df-8772-4c22-b5b4-b743dc4be974","version":"2.1.314","gitBranch":"HEAD"}24{"parentUuid":"494c9db0-a116-4251-b8ac-30751a0f0a0e","isSidechain":false,"promptId":"9ebd33b9-1875-4076-855f-328e8dae8857","type":"user","message":{"role":"user","content":[{"tool_use_id":"toolu_017tEkcJ9kzZey79YCMckaFc","type":"tool_result","content":" 1\tSOURCE EXTRACT — arxiv-2606.14621v1\n 2\tTitle: Evaluating the Impact of Rhode Island's Self-Sustaining Reemployment Services and Eligibility Assessment (RESEA) Program on Employment Outcomes\n 3\tAuthors: Harrison H. Li; Shanna Pearson-Merkowitz; David Yokum\n 4\tBibliographic record: arXiv:2606.14621v1 [econ.GN], submitted 12 Jun 2026 (version 1, the only version at retrieval). Abstract page: https://arxiv.org/abs/2606.14621v1\n 5\tRetrieved: https://arxiv.org/html/2606.14621v1 on 2026-10-30T03:23:18Z (SHA-256 of the retrieved HTML: f98fb1b39edd2107051cddf1da34aa8cf19e74e04d60bf9305a88cf966417da1)\n 6\tLicense: CC BY 4.0 (license shown on the arXiv abstract page; https://creativecommons.org/licenses/by/4.0/). Reproduced in part with attribution.\n 7\tExtract contents: title, authors and abstract; Section 3 'Results' (Table 2 with caption, the results paragraphs, Section 3.1 'Cost-benefit analysis'); from Section 4.1, Table 3 with its caption and the paragraph that discusses it.\n 8\tOmitted: Sections 1-2, Table 1, Section 3.2 (heterogeneous effects), the rest of Section 4, the references and the appendix.\n 9\tRendering note: converted from the HTML rendering to plain text. Tables are rendered one row per line with \" | \" separating cells; in regression tables the line following a coefficient row holds the standard errors in parentheses, exactly as printed. Mathematical expressions appear as LaTeX source; non-breaking spaces were replaced by ordinary spaces. No numbers were altered.\n 10\tEditorial note: Tables 2 and 3 were re-set in a one-row-per-outcome layout because the HTML rendering split each outcome over three rows and detached the p-values from their columns; the p-values and confidence intervals are attached to the column they belong to in the original (first p-value = treatment-control difference, second = average treatment effect).\n 11\t================================================================\n 12\t\n 13\t# Evaluating the Impact of Rhode Island's Self-Sustaining Reemployment Services and Eligibility Assessment (RESEA) Program on Employment Outcomes\n 14\t\n 15\tHarrison H. Li (Harvey Mudd College), Shanna Pearson-Merkowitz (University of Maryland, College Park), David Yokum (University of North Carolina at Chapel Hill)\n 16\t\n 17\t###### Abstract\n 18\t\n 19\tProlonged unemployment carries serious economic, health, and wellbeing costs. With federal support, most U.S. states now operate a Reemployment Services and Eligibility Assessment (RESEA) program to help Unemployment Insurance (UI) claimants return to work faster. We report results from a large (N = 23,549) preregistered randomized controlled trial (RCT) evaluating Rhode Island’s RESEA program from February 2022 to September 2023. We estimate that selection into the program increased annualized wages by $1,153, increased reemployment by 1.5 percentage points, and reduced UI duration by nearly two weeks. The vast majority of these wage and reemployment effects appeared within two quarters of claimants’ first pay dates and persisted through at least the following year, and we estimate that each dollar spent on the program saved the state $2.64. Using causal forests, a machine learning technique for estimating heterogeneous treatment effects (HTE), we also conduct an exploratory analysis to investigate if there are differential effects of selection into the RESEA program. We find that all participants experienced positive wage benefits from RESEA selection, with particularly large effects for older and lower-income workers. Finally, we improve upon prior RESEA evaluations by explicitly controlling for the week of treatment assignment — a methodological refinement absent from several existing RCTs of job-training programs that is important to eliminate confounding bias. We also discuss ways to harvest precision gains from baseline covariate adjustment without introducing large-sample bias.\n 20\t\n 21\t## 3 Results\n 22\t\n 23\t[Table 1 (pre-treatment characteristics) omitted from this extract.]\n 24\t\n 25\t[Table 2 — re-set by the extract editor from the HTML rendering, in which each outcome occupied three table rows; all values are verbatim. Columns: Outcome | Treatment | Control | Treatment-control difference | Average treatment effect estimate]\n 26\t\n 27\tOutcome | Treatment | Control | Treatment-control difference | Average treatment effect estimate\n 28\tWage | $33,073 (SD: 36,749) | $33,043 (SD: 36,231) | $29; p=0.95; 95% CI: [-903, 962] | $1,153; p=0.022; 95% CI: [166, 2,141]\n 29\tReemployment | 75.2% | 75.0% | 0.26 pp; p=0.64; 95% CI: [-0.84, 1.37] | 1.47 pp; p=0.013; 95% CI: [0.32, 2.62]\n 30\tWeeks on UI | 15.2 weeks (SD: 9.3) | 17.3 weeks (SD: 9.4) | -2.10 weeks; p<0.001; 95% CI: [-2.34, -1.86] | -1.99 weeks; p<0.001; 95% CI: [-2.24, -1.75]\n 31\tShort-term wage | $23,776 (SD: 31,948) | $23,897 (SD: 32,293) | -$121; p=0.77; 95% CI: [-941, 700] | $1,195; p=0.007; 95% CI: [326, 2,064]\n 32\tShort-term reemployment | 61.4% | 61.6% | -0.18 pp; p=0.77; 95% CI: [-1.43, 1.06] | 1.66 pp; p=0.012; 95% CI: [0.37, 2.96]\n 33\tShort-term weeks on UI | 14.2 weeks (SD: 8.4) | 15.9 weeks (SD: 8.3) | -1.70 weeks; p<0.001; 95% CI: [-1.92, -1.49] | -1.77 weeks; p<0.001; 95% CI: [-1.99, -1.55]\n 34\t\n 35\tTable 2: The average values of our long-term and short-term outcomes for the aggregate treatment and control groups in the study cohort, along with information about the differences in these averages between the treatment and control groups and our average treatment effect estimates. For the average outcomes, standard deviations are given in parentheses for the quantitative outcomes (wage and weeks on UI). For the treatment-control differences and the average treatment effect estimates, we provide two-sided p -values and 95% confidence intervals based on Welch’s two-sample t -test and the methodology described in the main text, respectively. The two rightmost columns illustrate how direct comparisons of outcome averages between the aggregate treatment and control groups can lead to significantly biased causal conclusions.\n 36\t\n 37\tOverall, we find that RESEA selection led to a statistically significant improvement in all three of the preregistered outcomes. RESEA selection led to a wage outcome that was $1,153 higher annually (95% CI: [$166, $2,141]; p=0.022 ), a 3.5% increase relative to the mean wage outcome of $33,043 in the control group (Table 2). There was also an estimated 1.47 percentage point increase in reemployment (95% CI: [0.32, 2.62]; p=0.013 ) and a 1.99 week reduction in the number of weeks on UI (95% CI: [1.75 weeks, 2.24 weeks]; p<0.001 ) due to RESEA selection. The latter is an 11.5% decrease compared to the mean control group weeks on UI outcome of 17.3 weeks. All three of these results remain statistically significant after correcting for multiple testing using Holm’s method to keep the familywise error rate below 5 percent.\n 38\t\n 39\tThe results for the short-term outcomes are substantively similar to those for the longer-term outcomes (Table 2). We estimate RESEA selection leads to a short-term wage outcome that is $1,195 higher (95% CI: [$326, $2,064]; p = 0.007) on an annualized basis and a 1.66 percentage point higher rate of short-term reemployment (95% CI: [0.37, 2.96]; p = 0.012). Given that the magnitudes of these causal estimates are very similar to those for the corresponding long-term outcomes, this suggests that the full impact of RESEA selection on wages and reemployment appears quickly by the second quarter after randomization, and persists for at least five quarters. We also find that those selected for RESEA spend 1.77 fewer weeks on UI in the benefit year of their claim (95% CI: [1.55 weeks, 1.99 weeks]; p ¡ 0.001). As this is a bit smaller than the effect size of 1.99 weeks estimated for the long term weeks on UI outcome, which includes an additional 26 weeks beyond the benefit year, we see some directional evidence that RESEA selection may also reduce the time spent on UI in the following year, suggesting that it may be helping claimants find employment that lasts longer, thereby reducing repetitive use of UI benefits.\n 40\t\n 41\tAs noted earlier, wages and reemployment are artificially zero-inflated due to missing out-of-state wage data. The Rhode Island job market is tightly integrated with those of the neighboring states of Massachusetts and Connecticut; the 2016-2020 5-Year American Community Survey found that nearly 16 percent of Rhode Island workers 16 years and older commuted out of state, mainly to Massachusetts. We note, however, that this missingness should not affect the directional validity of our causal analysis. This is because randomization ensures that this missingness is balanced between the treatment and control groups (within each block), unless RESEA selection itself differentially helps or hinders finding employment out of state or self-employment. To investigate this, we examined the presence of individuals who failed to exhaust their UI benefits in the benefit year of their claim while having $0 in reported RI wages for all of the five complete quarters after randomization. There were 3,325 claimants falling into this group, including 1,618 individuals (13.7%) in the aggregate control group and 1,707 individuals (14.6%) in the aggregate treatment group. After controlling for randomization week, this difference in proportions was not significant ( p = 0.55). The lack of statistical significance on this test with our large sample size along with the fact that the Rhode Island job database focuses overwhelmingly on jobs offered by Rhode Island employers suggests that RESEA selection does not differentially assist in finding out-of-state employment or self-employment.\n 42\t\n 43\t### 3.1 Cost-benefit analysis\n 44\t\n 45\tWe find that the decrease in time spent drawing UI benefits due to RESEA selection corresponds to a considerable cost savings to the state from paying out a smaller amount of UI benefits. We estimate that the average individual selected for RESEA during the study period drew $676 less (95% CI: [$563, $789], p<0.001 ) in UI benefits during the same benefit year of their claim than they would have if they were not selected for RESEA. This is a 9.9 percent reduction relative to the control group average of $6,839 in UI benefits drawn during the benefit year of the claim. Multiplying the estimate by the total number of individuals selected for RESEA in the study ( n=11,700 ) suggests that as a result of the program, the state paid out about $7.9 million fewer in UI benefits to claimants randomized during the study period over the same benefit year as their UI claims. This is much higher than the total expenditures of $2.99 million for the RESEA program over the study period, representing $2.64 in savings for the state budget for every $1 spent on the program.\n 46\t\n 47\t### 4.1 Methodological lessons (excerpt)\n 48\t\n 49\t[Table 3 — re-set by the extract editor from the HTML rendering; all values are verbatim. Columns: Outcome | Difference in means | Covariate adjusted | Fixed effects regression]\n 50\t\n 51\tOutcome | Difference in means | Covariate adjusted | Fixed effects regression\n 52\tWage | $1,153; p=0.022; 95% CI: [166, 2,141] | $1,137; p=0.014; 95% CI: [228, 2,047] | $1,100; p=0.027; 95% CI: [127, 2,073]\n 53\tReemployment | 1.47 pp; p=0.013; 95% CI: [0.32, 2.62] | 1.48 pp; p=0.012; 95% CI: [0.32, 2.63] | 1.49 pp; p=0.011; 95% CI: [0.34, 2.64]\n 54\tWeeks on UI | -1.99 wks; p<0.001; 95% CI: [-2.24, -1.75] | -1.93 wks; p<0.001; 95% CI: [-2.18, -1.68] | -1.97 wks; p<0.001; 95% CI: [-2.22, -1.72]\n 55\t\n 56\tTable 3: A comparison of the ITT estimates, two-sided p -values, and 95% confidence intervals for our primary outcomes from three different methodologies: the preregistered analysis based on eq. (1), the covariate adjusted analysis based on eq. (2), and the fixed effects regression in eq. (3). The leftmost column based on the preregistered analysis duplicates the rightmost column in Table 2 for ease of comparison.\n 57\t\n 58\tIf we directly compared treatment group and control group outcome averages without accounting for the week of randomization, the results would suggest RESEA selection had no detectable average effect on the wage and reemployment outcomes (column 4, Table 2). However, such an analysis is potentially biased under the experimental design because it does not respect the blocked randomization, which makes the week of randomization a known confounder. For example, weeks with a larger number of UI applicants, which had a higher proportion of control group individuals, tended to have lower-earning applicants (Fig. 7), thereby inflating the average wage outcome in the control group relative to the treatment group. This is critical because out of the thirteen publically available studies of RESEA-related employment assistance programs rated by CLEAR as having high causal evidence, six used block randomization like we do, yet only two of these (Black, Smith, Berger, & Noel., 2002; Klerman et al., 2019) properly adjusted for the block. Three others among these six studies used regression or matching methods in an attempt to control for observed demographic variables but not the block (Poe-Yamagata et al., 2011; Michaelides et al., 2012; Manoli et al., 2018), while the remaining study (Michaelides & Mueser, 2018) fit a linear regression model with the block indicators as fixed effects, as did two other more recent evaluations in Nevada (Michaelides & Mian, 2021; Brigandi et al., 2024) . 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Reproduced in part with attribution.\n 7\tExtract contents: title, authors and abstract; Section 3 'Results' (Table 2 with caption, the results paragraphs, Section 3.1 'Cost-benefit analysis'); from Section 4.1, Table 3 with its caption and the paragraph that discusses it.\n 8\tOmitted: Sections 1-2, Table 1, Section 3.2 (heterogeneous effects), the rest of Section 4, the references and the appendix.\n 9\tRendering note: converted from the HTML rendering to plain text. Tables are rendered one row per line with \" | \" separating cells; in regression tables the line following a coefficient row holds the standard errors in parentheses, exactly as printed. Mathematical expressions appear as LaTeX source; non-breaking spaces were replaced by ordinary spaces. No numbers were altered.\n 10\tEditorial note: Tables 2 and 3 were re-set in a one-row-per-outcome layout because the HTML rendering split each outcome over three rows and detached the p-values from their columns; the p-values and confidence intervals are attached to the column they belong to in the original (first p-value = treatment-control difference, second = average treatment effect).\n 11\t================================================================\n 12\t\n 13\t# Evaluating the Impact of Rhode Island's Self-Sustaining Reemployment Services and Eligibility Assessment (RESEA) Program on Employment Outcomes\n 14\t\n 15\tHarrison H. Li (Harvey Mudd College), Shanna Pearson-Merkowitz (University of Maryland, College Park), David Yokum (University of North Carolina at Chapel Hill)\n 16\t\n 17\t###### Abstract\n 18\t\n 19\tProlonged unemployment carries serious economic, health, and wellbeing costs. With federal support, most U.S. states now operate a Reemployment Services and Eligibility Assessment (RESEA) program to help Unemployment Insurance (UI) claimants return to work faster. We report results from a large (N = 23,549) preregistered randomized controlled trial (RCT) evaluating Rhode Island’s RESEA program from February 2022 to September 2023. We estimate that selection into the program increased annualized wages by $1,153, increased reemployment by 1.5 percentage points, and reduced UI duration by nearly two weeks. The vast majority of these wage and reemployment effects appeared within two quarters of claimants’ first pay dates and persisted through at least the following year, and we estimate that each dollar spent on the program saved the state $2.64. Using causal forests, a machine learning technique for estimating heterogeneous treatment effects (HTE), we also conduct an exploratory analysis to investigate if there are differential effects of selection into the RESEA program. We find that all participants experienced positive wage benefits from RESEA selection, with particularly large effects for older and lower-income workers. Finally, we improve upon prior RESEA evaluations by explicitly controlling for the week of treatment assignment — a methodological refinement absent from several existing RCTs of job-training programs that is important to eliminate confounding bias. We also discuss ways to harvest precision gains from baseline covariate adjustment without introducing large-sample bias.\n 20\t\n 21\t## 3 Results\n 22\t\n 23\t[Table 1 (pre-treatment characteristics) omitted from this extract.]\n 24\t\n 25\t[Table 2 — re-set by the extract editor from the HTML rendering, in which each outcome occupied three table rows; all values are verbatim. Columns: Outcome | Treatment | Control | Treatment-control difference | Average treatment effect estimate]\n 26\t\n 27\tOutcome | Treatment | Control | Treatment-control difference | Average treatment effect estimate\n 28\tWage | $33,073 (SD: 36,749) | $33,043 (SD: 36,231) | $29; p=0.95; 95% CI: [-903, 962] | $1,153; p=0.022; 95% CI: [166, 2,141]\n 29\tReemployment | 75.2% | 75.0% | 0.26 pp; p=0.64; 95% CI: [-0.84, 1.37] | 1.47 pp; p=0.013; 95% CI: [0.32, 2.62]\n 30\tWeeks on UI | 15.2 weeks (SD: 9.3) | 17.3 weeks (SD: 9.4) | -2.10 weeks; p<0.001; 95% CI: [-2.34, -1.86] | -1.99 weeks; p<0.001; 95% CI: [-2.24, -1.75]\n 31\tShort-term wage | $23,776 (SD: 31,948) | $23,897 (SD: 32,293) | -$121; p=0.77; 95% CI: [-941, 700] | $1,195; p=0.007; 95% CI: [326, 2,064]\n 32\tShort-term reemployment | 61.4% | 61.6% | -0.18 pp; p=0.77; 95% CI: [-1.43, 1.06] | 1.66 pp; p=0.012; 95% CI: [0.37, 2.96]\n 33\tShort-term weeks on UI | 14.2 weeks (SD: 8.4) | 15.9 weeks (SD: 8.3) | -1.70 weeks; p<0.001; 95% CI: [-1.92, -1.49] | -1.77 weeks; p<0.001; 95% CI: [-1.99, -1.55]\n 34\t\n 35\tTable 2: The average values of our long-term and short-term outcomes for the aggregate treatment and control groups in the study cohort, along with information about the differences in these averages between the treatment and control groups and our average treatment effect estimates. For the average outcomes, standard deviations are given in parentheses for the quantitative outcomes (wage and weeks on UI). For the treatment-control differences and the average treatment effect estimates, we provide two-sided p -values and 95% confidence intervals based on Welch’s two-sample t -test and the methodology described in the main text, respectively. The two rightmost columns illustrate how direct comparisons of outcome averages between the aggregate treatment and control groups can lead to significantly biased causal conclusions.\n 36\t\n 37\tOverall, we find that RESEA selection led to a statistically significant improvement in all three of the preregistered outcomes. RESEA selection led to a wage outcome that was $1,153 higher annually (95% CI: [$166, $2,141]; p=0.022 ), a 3.5% increase relative to the mean wage outcome of $33,043 in the control group (Table 2). There was also an estimated 1.47 percentage point increase in reemployment (95% CI: [0.32, 2.62]; p=0.013 ) and a 1.99 week reduction in the number of weeks on UI (95% CI: [1.75 weeks, 2.24 weeks]; p<0.001 ) due to RESEA selection. The latter is an 11.5% decrease compared to the mean control group weeks on UI outcome of 17.3 weeks. All three of these results remain statistically significant after correcting for multiple testing using Holm’s method to keep the familywise error rate below 5 percent.\n 38\t\n 39\tThe results for the short-term outcomes are substantively similar to those for the longer-term outcomes (Table 2). We estimate RESEA selection leads to a short-term wage outcome that is $1,195 higher (95% CI: [$326, $2,064]; p = 0.007) on an annualized basis and a 1.66 percentage point higher rate of short-term reemployment (95% CI: [0.37, 2.96]; p = 0.012). Given that the magnitudes of these causal estimates are very similar to those for the corresponding long-term outcomes, this suggests that the full impact of RESEA selection on wages and reemployment appears quickly by the second quarter after randomization, and persists for at least five quarters. We also find that those selected for RESEA spend 1.77 fewer weeks on UI in the benefit year of their claim (95% CI: [1.55 weeks, 1.99 weeks]; p ¡ 0.001). As this is a bit smaller than the effect size of 1.99 weeks estimated for the long term weeks on UI outcome, which includes an additional 26 weeks beyond the benefit year, we see some directional evidence that RESEA selection may also reduce the time spent on UI in the following year, suggesting that it may be helping claimants find employment that lasts longer, thereby reducing repetitive use of UI benefits.\n 40\t\n 41\tAs noted earlier, wages and reemployment are artificially zero-inflated due to missing out-of-state wage data. The Rhode Island job market is tightly integrated with those of the neighboring states of Massachusetts and Connecticut; the 2016-2020 5-Year American Community Survey found that nearly 16 percent of Rhode Island workers 16 years and older commuted out of state, mainly to Massachusetts. We note, however, that this missingness should not affect the directional validity of our causal analysis. This is because randomization ensures that this missingness is balanced between the treatment and control groups (within each block), unless RESEA selection itself differentially helps or hinders finding employment out of state or self-employment. To investigate this, we examined the presence of individuals who failed to exhaust their UI benefits in the benefit year of their claim while having $0 in reported RI wages for all of the five complete quarters after randomization. There were 3,325 claimants falling into this group, including 1,618 individuals (13.7%) in the aggregate control group and 1,707 individuals (14.6%) in the aggregate treatment group. After controlling for randomization week, this difference in proportions was not significant ( p = 0.55). The lack of statistical significance on this test with our large sample size along with the fact that the Rhode Island job database focuses overwhelmingly on jobs offered by Rhode Island employers suggests that RESEA selection does not differentially assist in finding out-of-state employment or self-employment.\n 42\t\n 43\t### 3.1 Cost-benefit analysis\n 44\t\n 45\tWe find that the decrease in time spent drawing UI benefits due to RESEA selection corresponds to a considerable cost savings to the state from paying out a smaller amount of UI benefits. We estimate that the average individual selected for RESEA during the study period drew $676 less (95% CI: [$563, $789], p<0.001 ) in UI benefits during the same benefit year of their claim than they would have if they were not selected for RESEA. This is a 9.9 percent reduction relative to the control group average of $6,839 in UI benefits drawn during the benefit year of the claim. Multiplying the estimate by the total number of individuals selected for RESEA in the study ( n=11,700 ) suggests that as a result of the program, the state paid out about $7.9 million fewer in UI benefits to claimants randomized during the study period over the same benefit year as their UI claims. This is much higher than the total expenditures of $2.99 million for the RESEA program over the study period, representing $2.64 in savings for the state budget for every $1 spent on the program.\n 46\t\n 47\t### 4.1 Methodological lessons (excerpt)\n 48\t\n 49\t[Table 3 — re-set by the extract editor from the HTML rendering; all values are verbatim. Columns: Outcome | Difference in means | Covariate adjusted | Fixed effects regression]\n 50\t\n 51\tOutcome | Difference in means | Covariate adjusted | Fixed effects regression\n 52\tWage | $1,153; p=0.022; 95% CI: [166, 2,141] | $1,137; p=0.014; 95% CI: [228, 2,047] | $1,100; p=0.027; 95% CI: [127, 2,073]\n 53\tReemployment | 1.47 pp; p=0.013; 95% CI: [0.32, 2.62] | 1.48 pp; p=0.012; 95% CI: [0.32, 2.63] | 1.49 pp; p=0.011; 95% CI: [0.34, 2.64]\n 54\tWeeks on UI | -1.99 wks; p<0.001; 95% CI: [-2.24, -1.75] | -1.93 wks; p<0.001; 95% CI: [-2.18, -1.68] | -1.97 wks; p<0.001; 95% CI: [-2.22, -1.72]\n 55\t\n 56\tTable 3: A comparison of the ITT estimates, two-sided p -values, and 95% confidence intervals for our primary outcomes from three different methodologies: the preregistered analysis based on eq. (1), the covariate adjusted analysis based on eq. (2), and the fixed effects regression in eq. (3). The leftmost column based on the preregistered analysis duplicates the rightmost column in Table 2 for ease of comparison.\n 57\t\n 58\tIf we directly compared treatment group and control group outcome averages without accounting for the week of randomization, the results would suggest RESEA selection had no detectable average effect on the wage and reemployment outcomes (column 4, Table 2). However, such an analysis is potentially biased under the experimental design because it does not respect the blocked randomization, which makes the week of randomization a known confounder. For example, weeks with a larger number of UI applicants, which had a higher proportion of control group individuals, tended to have lower-earning applicants (Fig. 7), thereby inflating the average wage outcome in the control group relative to the treatment group. 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Each extract begins with a provenance header (title, authors, bibliographic record, retrieval URL and UTC, SHA-256 of the retrieved HTML, license, list of included and omitted sections). Only the excerpts needed for the task are reproduced; everything else is omitted. Tables are rendered one row per line with ` | ` between cells; in regression tables, the line following a coefficient row holds the standard errors in parentheses as printed in the original.\n\n| file | document | retrieval UTC | license | SHA-256 of the extract |\n|---|---|---|---|---|\n| `sources/arxiv-2609.27732v1.txt` | Armendariz, A. (2026). Do Drug Consumption Rooms Reduce Drug-Related Hospitalizations? Evidence from Switzerland. arXiv:2609.27732v1 [econ.GN]. https://arxiv.org/abs/2609.27732v1 (full text: https://arxiv.org/html/2609.27732v1) | 2026-10-30T03:23:18Z | CC BY 4.0 | ee2d444d2f78f2af2ca2cf69b59a61fcd7ac5e10ea29e8ddcd67917bf07d6a8b |\n| `sources/arxiv-2606.14621v1.txt` | Li, H. 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Evidence from Switzerland\n 3\tAuthors: Ana Armendariz (University of St. Gallen)\n 4\tBibliographic record: arXiv:2609.27732v1 [econ.GN], submitted 23 Sep 2026 (version 1, the only version at retrieval). Abstract page: https://arxiv.org/abs/2609.27732v1\n 5\tRetrieved: https://arxiv.org/html/2609.27732v1 on 2026-10-30T03:23:18Z (SHA-256 of the retrieved HTML: 22b06050f4ff6e665aedd80561fa4031b1717867ecfeca71d1d2902ee1b09f52)\n 6\tLicense: CC BY 4.0 (license shown on the arXiv abstract page; https://creativecommons.org/licenses/by/4.0/). Reproduced in part with attribution.\n 7\tExtract contents: title, author, date and abstract; Section 6 'Results' in full (Figure notes, Table 6, Table 7, Section 6.1 'Mechanisms'); Appendix Table A19 with its note and the paragraph that discusses it.\n 8\tOmitted: Sections 1-5 and 7, the other appendix tables and figures, the references.\n 9\tRendering note: converted from the HTML rendering to plain text. Tables are rendered one row per line with \" | \" separating cells; in regression tables the line following a coefficient row holds the standard errors in parentheses, exactly as printed. Mathematical expressions appear as LaTeX source; non-breaking spaces were replaced by ordinary spaces. No numbers were altered.\n 10\t================================================================\n 11\t\n 12\t# Do Drug Consumption Rooms Reduce Drug-Related Hospitalizations? Evidence from Switzerland\n 13\t\n 14\tAna Armendariz*\n 15\t\n 16\tSeptember 23, 2026\n 17\t\n 18\tThis paper estimates the causal effect of drug consumption room (DCR) openings on drug-related hospitalizations in Switzerland. I exploit the staggered introduction of DCRs across Swiss cities between 1998 and 2022, using individual-level hospital records and a difference-in-differences estimator. DCR openings reduce drug-related hospitalization rates by roughly 35% within 5 km of a facility. The reduction is most pronounced for fatal outcomes, which fall by 35% while narcotics poisoning hospitalizations rise by a comparable amount, consistent with DCRs converting potentially fatal overdoses into non-fatal hospitalizations. Mental and behavioral disorder hospitalizations decline by 32% while estimates for Hepatitis and HIV are imprecise. The findings support the role of DCRs as an effective harm reduction strategy.\n 19\t\n 20\tKeywords: Drug Consumption Rooms, Harm Reduction, Hospitalizations, Drugs, Public Health, Causal Inference\n 21\t\n 22\t## 6 Results\n 23\t\n 24\tThis section reports the effect of DCR openings on the rate of drug-related hospitalizations per 100,000 inhabitants. I begin with the event-study estimates and then present the overall pooled ATT. I then disaggregate the overall outcome into its sub-outcome categories and report the same estimates for each.\n 25\t\n 26\tFigure 6: Event study estimates by buffer zone, \\pm 5-year window\n 27\t\n 28\tNote: The figure plots event-study coefficients from the doubly robust estimator of Callaway and Sant’Anna (2021) for regions within 5 km of a DCR opening. The comparison group consists of never-treated regions (608 control regions). The outcome is the log drug-related hospitalization rate per 100,000 inhabitants. The sample includes all staggered-treated MedStat regions within 5 km of a DCR that opened between 1998 and 2022 and all never-treated regions. The estimation uses a \\pm 5-year window relative to DCR opening, with t=-5 and t=+5 representing pooled endpoint bins that absorb all periods beyond the window. The reference period is a universal base period. Regions near DCRs that opened before 1998 (always-treated) are excluded through out. 95% confidence intervals are based on standard errors clustered at the MedStat region level. Results for the 1 km and 3 km buffer specifications are reported in Appendix Figure A17.\n 29\t\n 30\tFigure 6 presents the event study estimates for the 5 km buffer specifications. I focus on the 5 km buffer specification, as it includes the largest number of treated regions and yields the most precise estimates. I summarize dynamic effects over a symmetric five year window around DCR openings. This window avoids relying on distant leads and lags that are informed by only a small subset of adopters. Pre-treatment coefficients are small and statistically insignificant, supporting the parallel trends assumption. The post-treatment coefficients are consistently negative, indicating a reduction in drug-related hospitalizations following DCR openings. The estimates of the overall summary of ATTs based on calendar time aggregation of Callaway and Sant’Anna (2021) is around -35% reduction in hospitalizations due to drugs.\n 31\t\n 32\tTable 6: Overall Average Treatment Effect on the Treated (ATT)\n 33\t\n 34\t| 1 km | 3 km | 5 km\n 35\t\n 36\tATT | -0.399 | -0.283 | -0.431**\n 37\t\n 38\t| (0.412) | (0.279) | (0.210)\n 39\t\n 40\t% change | -32.9% | -24.7% | -35.0%\n 41\t\n 42\tTreated regions | 7 | 35 | 50\n 43\t\n 44\tControl regions | 608 | 608 | 608\n 45\t\n 46\tObservations | 16,175 | 16,875 | 17,250\n 47\t\n 48\tNote: The table reports the overall ATT estimated using the doubly robust Callaway and Sant’Anna (2021) estimator with never-treated controls and a universal base period. The outcome is the log drug-related hospitalization rate per 100,000 inhabitants. Columns differ in the geographic buffer used to define treated Medstat regions. The control group consists of 608 never-treated Medstat regions\n 49\tthroughout. Regions near DCRs that opened before 1998\n 50\t(always-treated) are excluded. Standard errors clustered at the Medstat region level in\n 51\tparentheses. Significance: {}^{***}p<0.01 , {}^{**}p<0.05 ,\n 52\t{}^{*}p<0.10 .\n 53\t\n 54\tTable 6 reports the pooled ATT for the 1 km, 3 km and 5 km buffer specification, aggregating the dynamic treatment effects into a single estimate averaged across all post-treatment periods and cohorts. The 5 km specification, yields an ATT of -0.431\n 55\tcorresponding to a 35% reduction in the drug-related hospitalization rate. This estimate is statistically significant at the 5% level. The 3 km and 1 km estimates point in the same direction but are less precise, due to the smaller number of treated regions.\n 56\t\n 57\tTo further explore the mechanisms through which DCR openings affect drug-related hospitalizations, I disaggregate the main outcome into five diagnostic\n 58\tsub-categories: (i) mental and behavioral disorders due to psychoactive substance use, (ii) viral hepatitis, (iii) HIV, (iv) poisoning by narcotics and psychodysleptics, and (v) fatal drug-related hospitalizations. Accidental poisoning is excluded due to the very small number of cases.\n 59\t\n 60\tFigure 7: Event study: Sub-outcome estimates,\n 61\twithin 5 km, \\pm 5-year window\n 62\t\n 63\tNote: The figure plots event-study coefficients from the doubly robust Callaway & Sant’Anna (2021) estimator for four diagnostic sub-categories of drug-related hospitalizations. Each panel uses a separate y -axis to accommodate differences in scale across outcomes. The sample includes all staggered-treated MedStat regions within 5 km of a\n 64\tDCR that opened between 1998 and 2022. The reference period is a universal base period. Regions near DCRs that opened before 1998 (always-treated) are excluded. 95% confidence intervals are based on standard errors clustered at the MedStat region level.\n 65\t\n 66\tTable 7: Overall ATT by Outcome Category and Buffer Zone\n 67\t\n 68\tOutcome | 1 km | 3 km | 5 km\n 69\t\n 70\tMental/Behavioral | -0.354 | -0.202 | -0.381*\n 71\t\n 72\t| (0.382) | (0.244) | (0.220)\n 73\t\n 74\tHepatitis | -0.270 | -0.413 | -0.406\n 75\t\n 76\t| (0.486) | (0.270) | (0.250)\n 77\t\n 78\tHIV | 0.063 | -0.239 | -0.340\n 79\t\n 80\t| (0.801) | (0.337) | (0.294)\n 81\t\n 82\tNarcotics | 1.186*** | 0.549*** | 0.390**\n 83\t\n 84\t| (0.288) | (0.187) | (0.165)\n 85\t\n 86\tDrug-related (fatal) | -1.207*** | -0.290 | -0.354**\n 87\t\n 88\t| (0.137) | (0.215) | (0.178)\n 89\t\n 90\tTreated regions | 7 | 35 | 50\n 91\t\n 92\tControl regions | 608 (never-treated) | |\n 93\t\n 94\tNote: Each cell reports the overall ATT from\n 95\tthe doubly robust Callaway & Sant’Anna (2021) estimator with\n 96\tnever-treated controls and a universal base period. Outcomes are\n 97\tlog hospitalization rates per 100,000 inhabitants. Sub-outcomes:\n 98\tmental and behavioral disorders (F11–F19), viral hepatitis (B15–B19),\n 99\tHIV disease (B20–B24), narcotics/psychodysleptics (T40). The 1 km\n 100\testimates are identified from a single treated region per cohort and\n 101\tshould be interpreted with caution. Regions near DCRs opened before\n 102\t1998 excluded. Standard errors clustered at the Medstat region level.\n 103\tSignificance: {}^{***}p<0.01 , {}^{**}p<0.05 , {}^{*}p<0.10 .\n 104\t\n 105\tFigure 7 and Table 7 repeat the estimation for the five diagnostic categories. From Table 7, the ATT estimates for hospitalizations due to mental and behavioral disorders are consistently negative and marginally significant at the 5 km buffer specification. Moreover, the estimates of hepatitis are also negative and of comparable magnitude but insignificant. However, the event-study path in Figure 7 shows a gradual decline that builds from year 3 onward, consistent with a slow-acting reduction in needle sharing. HIV estimates are insignificant and close to zero. Narcotics poisoning hospitalizations rise after DCR opening and remain positive across all buffers. Lastly, fatal drug-related hospitalizations move in the opposite direction, falling after opening the DCR. The opposing patterns in narcotics and fatal hospitalizations suggest that DCRs convert events that would otherwise be fatal into survivable hospital contacts.\n 106\t\n 107\t### 6.1 Mechanisms\n 108\t\n 109\tThe sub-outcome results point to two channels through which DCRs reduce drug-related hospitalizations. The first is overdose supervision. DCRs provide a medically supervised environment where staff can control the dose consumed, perform resuscitation, and call emergency services when an overdose occurs. When supervision prevents a death that would otherwise happen outside a hospital, the consequence is a simultaneous decline in fatal drug-related hospitalizations and a rise in non-fatal poisoning contacts, as events that would have ended in death instead end in a hospital visit. The results are consistent with this prediction. Drug-related fatal hospitalizations fall near DCRs, by approximately 30% at 5 km, while narcotics and psychodysleptics hospitalizations rise by 47% at 5 km. The opposing signs and spatial concentration of these two effects are consistent with a\n 110\tsubstitution from out-of-hospital mortality to in-hospital survival. Since I cannot observe overdose events that do not result in a hospital contact, this interpretation is suggestive rather than identified, but it is consistent with the clinical evidence on DCR-based overdose reversals\n 111\t(Kerr et al., 2017; Hedrich, 2004).\n 112\t\n 113\tThe second channel is harm reduction for blood-borne diseases. DCRs distribute sterile injection equipment, which reduces needle sharing and the transmission of viral hepatitis and HIV. Unlike overdose prevention, these effects are expected to emerge slowly, since disease progression and hospitalization take years to follow from initial infection. The event-study path for hepatitis is consistent with this lag. The estimates are close to zero in the first two post-treatment years and become progressively more negative from year 3 onward, reaching approximately 40% below baseline by year 5. HIV estimates are near zero through out the analysis, with wide confidence intervals. A longer panel and additional out-patient data would be needed to determine whether these trends continue and to get more precise estimates.\n 114\t\n 115\tA third potential channel is referral to treatment and social services. DCRs routinely connect users to addiction treatment, primary care, and housing support, and a sustained reduction in hospitalizations could partly reflect better long-term management of drug dependence. The regional hospitalization panel used in this paper does not contain information on treatment entry or service use, so I cannot separate this channel from the two described above. It remains a plausible additional mechanism that future work with information on treatment take up data could examine.\n 116\t\n 117\tTable A19: Robustness: Overall ATT Across Estimators — 5 km buffer, \\pm 5-year window\n 118\t\n 119\t| CS-DR | Sun & Abraham | Synthetic DiD | Stacked DiD\n 120\t\n 121\tATT | -0.431** | -0.438** | -0.362* | -0.149***\n 122\t\n 123\t| (0.218) | (0.208) | (0.205) | (0.038)\n 124\t\n 125\t% change | -35.0% | -35.5% | -30.3% | -13.9%\n 126\t\n 127\tTreated regions | 50 | | |\n 128\t\n 129\tControl regions | 608 | | |\n 130\t\n 131\tObservations | 17,250 | | |\n 132\t\n 133\tNote: All specifications use the 5 km buffer,\n 134\tnever-treated comparison regions (640 regions), and a \\pm 5-year window","is_error":false},{"tool_use_id":"toolu_017tEkcJ9kzZey79YCMckaFc","type":"tool_result","content":" 1\tSOURCE EXTRACT — arxiv-2606.14621v1\n 2\tTitle: Evaluating the Impact of Rhode Island's Self-Sustaining Reemployment Services and Eligibility Assessment (RESEA) Program on Employment Outcomes\n 3\tAuthors: Harrison H. Li; Shanna Pearson-Merkowitz; David Yokum\n 4\tBibliographic record: arXiv:2606.14621v1 [econ.GN], submitted 12 Jun 2026 (version 1, the only version at retrieval). Abstract page: https://arxiv.org/abs/2606.14621v1\n 5\tRetrieved: https://arxiv.org/html/2606.14621v1 on 2026-10-30T03:23:18Z (SHA-256 of the retrieved HTML: f98fb1b39edd2107051cddf1da34aa8cf19e74e04d60bf9305a88cf966417da1)\n 6\tLicense: CC BY 4.0 (license shown on the arXiv abstract page; https://creativecommons.org/licenses/by/4.0/). Reproduced in part with attribution.\n 7\tExtract contents: title, authors and abstract; Section 3 'Results' (Table 2 with caption, the results paragraphs, Section 3.1 'Cost-benefit analysis'); from Section 4.1, Table 3 with its caption and the paragraph that discusses it.\n 8\tOmitted: Sections 1-2, Table 1, Section 3.2 (heterogeneous effects), the rest of Section 4, the references and the appendix.\n 9\tRendering note: converted from the HTML rendering to plain text. Tables are rendered one row per line with \" | \" separating cells; in regression tables the line following a coefficient row holds the standard errors in parentheses, exactly as printed. Mathematical expressions appear as LaTeX source; non-breaking spaces were replaced by ordinary spaces. No numbers were altered.\n 10\tEditorial note: Tables 2 and 3 were re-set in a one-row-per-outcome layout because the HTML rendering split each outcome over three rows and detached the p-values from their columns; the p-values and confidence intervals are attached to the column they belong to in the original (first p-value = treatment-control difference, second = average treatment effect).\n 11\t================================================================\n 12\t\n 13\t# Evaluating the Impact of Rhode Island's Self-Sustaining Reemployment Services and Eligibility Assessment (RESEA) Program on Employment Outcomes\n 14\t\n 15\tHarrison H. Li (Harvey Mudd College), Shanna Pearson-Merkowitz (University of Maryland, College Park), David Yokum (University of North Carolina at Chapel Hill)\n 16\t\n 17\t###### Abstract\n 18\t\n 19\tProlonged unemployment carries serious economic, health, and wellbeing costs. With federal support, most U.S. states now operate a Reemployment Services and Eligibility Assessment (RESEA) program to help Unemployment Insurance (UI) claimants return to work faster. We report results from a large (N = 23,549) preregistered randomized controlled trial (RCT) evaluating Rhode Island’s RESEA program from February 2022 to September 2023. We estimate that selection into the program increased annualized wages by $1,153, increased reemployment by 1.5 percentage points, and reduced UI duration by nearly two weeks. The vast majority of these wage and reemployment effects appeared within two quarters of claimants’ first pay dates and persisted through at least the following year, and we estimate that each dollar spent on the program saved the state $2.64. Using causal forests, a machine learning technique for estimating heterogeneous treatment effects (HTE), we also conduct an exploratory analysis to investigate if there are differential effects of selection into the RESEA program. We find that all participants experienced positive wage benefits from RESEA selection, with particularly large effects for older and lower-income workers. Finally, we improve upon prior RESEA evaluations by explicitly controlling for the week of treatment assignment — a methodological refinement absent from several existing RCTs of job-training programs that is important to eliminate confounding bias. We also discuss ways to harvest precision gains from baseline covariate adjustment without introducing large-sample bias.\n 20\t\n 21\t## 3 Results\n 22\t\n 23\t[Table 1 (pre-treatment characteristics) omitted from this extract.]\n 24\t\n 25\t[Table 2 — re-set by the extract editor from the HTML rendering, in which each outcome occupied three table rows; all values are verbatim. Columns: Outcome | Treatment | Control | Treatment-control difference | Average treatment effect estimate]\n 26\t\n 27\tOutcome | Treatment | Control | Treatment-control difference | Average treatment effect estimate\n 28\tWage | $33,073 (SD: 36,749) | $33,043 (SD: 36,231) | $29; p=0.95; 95% CI: [-903, 962] | $1,153; p=0.022; 95% CI: [166, 2,141]\n 29\tReemployment | 75.2% | 75.0% | 0.26 pp; p=0.64; 95% CI: [-0.84, 1.37] | 1.47 pp; p=0.013; 95% CI: [0.32, 2.62]\n 30\tWeeks on UI | 15.2 weeks (SD: 9.3) | 17.3 weeks (SD: 9.4) | -2.10 weeks; p<0.001; 95% CI: [-2.34, -1.86] | -1.99 weeks; p<0.001; 95% CI: [-2.24, -1.75]\n 31\tShort-term wage | $23,776 (SD: 31,948) | $23,897 (SD: 32,293) | -$121; p=0.77; 95% CI: [-941, 700] | $1,195; p=0.007; 95% CI: [326, 2,064]\n 32\tShort-term reemployment | 61.4% | 61.6% | -0.18 pp; p=0.77; 95% CI: [-1.43, 1.06] | 1.66 pp; p=0.012; 95% CI: [0.37, 2.96]\n 33\tShort-term weeks on UI | 14.2 weeks (SD: 8.4) | 15.9 weeks (SD: 8.3) | -1.70 weeks; p<0.001; 95% CI: [-1.92, -1.49] | -1.77 weeks; p<0.001; 95% CI: [-1.99, -1.55]\n 34\t\n 35\tTable 2: The average values of our long-term and short-term outcomes for the aggregate treatment and control groups in the study cohort, along with information about the differences in these averages between the treatment and control groups and our average treatment effect estimates. For the average outcomes, standard deviations are given in parentheses for the quantitative outcomes (wage and weeks on UI). For the treatment-control differences and the average treatment effect estimates, we provide two-sided p -values and 95% confidence intervals based on Welch’s two-sample t -test and the methodology described in the main text, respectively. The two rightmost columns illustrate how direct comparisons of outcome averages between the aggregate treatment and control groups can lead to significantly biased causal conclusions.\n 36\t\n 37\tOverall, we find that RESEA selection led to a statistically significant improvement in all three of the preregistered outcomes. RESEA selection led to a wage outcome that was $1,153 higher annually (95% CI: [$166, $2,141]; p=0.022 ), a 3.5% increase relative to the mean wage outcome of $33,043 in the control group (Table 2). There was also an estimated 1.47 percentage point increase in reemployment (95% CI: [0.32, 2.62]; p=0.013 ) and a 1.99 week reduction in the number of weeks on UI (95% CI: [1.75 weeks, 2.24 weeks]; p<0.001 ) due to RESEA selection. The latter is an 11.5% decrease compared to the mean control group weeks on UI outcome of 17.3 weeks. All three of these results remain statistically significant after correcting for multiple testing using Holm’s method to keep the familywise error rate below 5 percent.\n 38\t\n 39\tThe results for the short-term outcomes are substantively similar to those for the longer-term outcomes (Table 2). We estimate RESEA selection leads to a short-term wage outcome that is $1,195 higher (95% CI: [$326, $2,064]; p = 0.007) on an annualized basis and a 1.66 percentage point higher rate of short-term reemployment (95% CI: [0.37, 2.96]; p = 0.012). Given that the magnitudes of these causal estimates are very similar to those for the corresponding long-term outcomes, this suggests that the full impact of RESEA selection on wages and reemployment appears quickly by the second quarter after randomization, and persists for at least five quarters. We also find that those selected for RESEA spend 1.77 fewer weeks on UI in the benefit year of their claim (95% CI: [1.55 weeks, 1.99 weeks]; p ¡ 0.001). As this is a bit smaller than the effect size of 1.99 weeks estimated for the long term weeks on UI outcome, which includes an additional 26 weeks beyond the benefit year, we see some directional evidence that RESEA selection may also reduce the time spent on UI in the following year, suggesting that it may be helping claimants find employment that lasts longer, thereby reducing repetitive use of UI benefits.\n 40\t\n 41\tAs noted earlier, wages and reemployment are artificially zero-inflated due to missing out-of-state wage data. The Rhode Island job market is tightly integrated with those of the neighboring states of Massachusetts and Connecticut; the 2016-2020 5-Year American Community Survey found that nearly 16 percent of Rhode Island workers 16 years and older commuted out of state, mainly to Massachusetts. We note, however, that this missingness should not affect the directional validity of our causal analysis. This is because randomization ensures that this missingness is balanced between the treatment and control groups (within each block), unless RESEA selection itself differentially helps or hinders finding employment out of state or self-employment. To investigate this, we examined the presence of individuals who failed to exhaust their UI benefits in the benefit year of their claim while having $0 in reported RI wages for all of the five complete quarters after randomization. There were 3,325 claimants falling into this group, including 1,618 individuals (13.7%) in the aggregate control group and 1,707 individuals (14.6%) in the aggregate treatment group. After controlling for randomization week, this difference in proportions was not significant ( p = 0.55). The lack of statistical significance on this test with our large sample size along with the fact that the Rhode Island job database focuses overwhelmingly on jobs offered by Rhode Island employers suggests that RESEA selection does not differentially assist in finding out-of-state employment or self-employment.\n 42\t\n 43\t### 3.1 Cost-benefit analysis\n 44\t\n 45\tWe find that the decrease in time spent drawing UI benefits due to RESEA selection corresponds to a considerable cost savings to the state from paying out a smaller amount of UI benefits. We estimate that the average individual selected for RESEA during the study period drew $676 less (95% CI: [$563, $789], p<0.001 ) in UI benefits during the same benefit year of their claim than they would have if they were not selected for RESEA. This is a 9.9 percent reduction relative to the control group average of $6,839 in UI benefits drawn during the benefit year of the claim. Multiplying the estimate by the total number of individuals selected for RESEA in the study ( n=11,700 ) suggests that as a result of the program, the state paid out about $7.9 million fewer in UI benefits to claimants randomized during the study period over the same benefit year as their UI claims. This is much higher than the total expenditures of $2.99 million for the RESEA program over the study period, representing $2.64 in savings for the state budget for every $1 spent on the program.\n 46\t\n 47\t### 4.1 Methodological lessons (excerpt)\n 48\t\n 49\t[Table 3 — re-set by the extract editor from the HTML rendering; all values are verbatim. Columns: Outcome | Difference in means | Covariate adjusted | Fixed effects regression]\n 50\t\n 51\tOutcome | Difference in means | Covariate adjusted | Fixed effects regression\n 52\tWage | $1,153; p=0.022; 95% CI: [166, 2,141] | $1,137; p=0.014; 95% CI: [228, 2,047] | $1,100; p=0.027; 95% CI: [127, 2,073]\n 53\tReemployment | 1.47 pp; p=0.013; 95% CI: [0.32, 2.62] | 1.48 pp; p=0.012; 95% CI: [0.32, 2.63] | 1.49 pp; p=0.011; 95% CI: [0.34, 2.64]\n 54\tWeeks on UI | -1.99 wks; p<0.001; 95% CI: [-2.24, -1.75] | -1.93 wks; p<0.001; 95% CI: [-2.18, -1.68] | -1.97 wks; p<0.001; 95% CI: [-2.22, -1.72]\n 55\t\n 56\tTable 3: A comparison of the ITT estimates, two-sided p -values, and 95% confidence intervals for our primary outcomes from three different methodologies: the preregistered analysis based on eq. (1), the covariate adjusted analysis based on eq. (2), and the fixed effects regression in eq. (3). The leftmost column based on the preregistered analysis duplicates the rightmost column in Table 2 for ease of comparison.\n 57\t\n 58\tIf we directly compared treatment group and control group outcome averages without accounting for the week of randomization, the results would suggest RESEA selection had no detectable average effect on the wage and reemployment outcomes (column 4, Table 2). However, such an analysis is potentially biased under the experimental design because it does not respect the blocked randomization, which makes the week of randomization a known confounder. For example, weeks with a larger number of UI applicants, which had a higher proportion of control group individuals, tended to have lower-earning applicants (Fig. 7), thereby inflating the average wage outcome in the control group relative to the treatment group. This is critical because out of the thirteen publically available studies of RESEA-related employment assistance programs rated by CLEAR as having high causal evidence, six used block randomization like we do, yet only two of these (Black, Smith, Berger, & Noel., 2002; Klerman et al., 2019) properly adjusted for the block. Three others among these six studies used regression or matching methods in an attempt to control for observed demographic variables but not the block (Poe-Yamagata et al., 2011; Michaelides et al., 2012; Manoli et al., 2018), while the remaining study (Michaelides & Mueser, 2018) fit a linear regression model with the block indicators as fixed effects, as did two other more recent evaluations in Nevada (Michaelides & Mian, 2021; Brigandi et al., 2024) . These fixed effects regressions amount to estimating the coefficient in the regression 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-p out/state && cd out/state && cat > contract.md <<'EOF'\n# Contract (P0) — F4-conf-02\n**Question.** For each of six literature-review assertions (data/assertions.json), decide from the cited source extract alone whether it is supported / not_supported / not_assessable.\n**Estimands.** Six categorical verdicts (A1–A6), each with one locator and a one-sentence reason. 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Conventions: % change = 100(exp(b)-1); 95% CI = b ± 1.96·SE (2.0 acceptable).\n**Outputs.** out/results.json keys: verdicts, locators, reasons, n_supported, n_not_supported, n_not_assessable, task_id (\"F4-conf-02\"), feasibility, feasibility_reason, data_issues, n_input_rows, n_analysed, random_seed (null). out/report.md (Question; Data and exclusions; Method; Results; Uncertainty; Limitations and open issues). out/analysis.py (deterministic, reads data/ only, prints relied-on source lines). out/claims.json.\n**Information rules.** Only the extracts are evidence; no memory of papers/other versions/outside knowledge.\n**Invalidity.** Using outside knowledge; missing/unreadable extracts; verdicts not traceable to a locator.\nEOF\ncat > phases.json <<'EOF'\n{\"P0\":{\"status\":\"passed\",\"checks\":[\"TASK.md read fully\",\"contract.md 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Meaningful only under the stated rules: every element (sign, magnitude, uncertainty, significance, population) must hold for \"supported\"; any contradicted element => not_supported; not_assessable only when the extract contains no bearing quantity. Conventions: % change = 100(exp(b)-1); 95% CI = b ± 1.96·SE (2.0 acceptable).\n**Outputs.** out/results.json keys: verdicts, locators, reasons, n_supported, n_not_supported, n_not_assessable, task_id (\"F4-conf-02\"), feasibility, feasibility_reason, data_issues, n_input_rows, n_analysed, random_seed (null). out/report.md (Question; Data and exclusions; Method; Results; Uncertainty; Limitations and open issues). out/analysis.py (deterministic, reads data/ only, prints relied-on source lines). out/claims.json.\n**Information rules.** Only the extracts are evidence; no memory of papers/other versions/outside knowledge.\n**Invalidity.** Using outside knowledge; missing/unreadable extracts; verdicts not traceable to a locator.\nEOF\ncat > phases.json <<'EOF'\n{\"P0\":{\"status\":\"passed\",\"checks\":[\"TASK.md read fully\",\"contract.md written\"],\"notes\":\"\"},\n\"P1\":{\"status\":\"running\",\"checks\":[],\"notes\":\"\"},\n\"P2\":{\"status\":\"pending\",\"checks\":[],\"notes\":\"\"},\n\"P3\":{\"status\":\"pending\",\"checks\":[],\"notes\":\"\"},\n\"P4\":{\"status\":\"pending\",\"checks\":[],\"notes\":\"\"},\n\"P5\":{\"status\":\"pending\",\"checks\":[],\"notes\":\"\"}}\nEOF\necho \"- 2026-10-30 P0 passed: contract written.\" > log.md","description":"Write contract, phase ledger, log"}}]}}34{"type":"api-request","sessionId":"989b99df-8772-4c22-b5b4-b743dc4be974","id":"6359c90a-6ae4-490c-a4d0-43b253880b80","timestamp":"2026-10-30T05:29:25.285Z","version":"2.1.314","querySource":"sdk","shapeHash":"ca65346191cc3fbfd9b5075f5cd1e1d20265b723edff78ec161d4675b9c87931","params":{"model":"claude-opus-5-5","betas":["claude-code-20250219","interleaved-thinking-2025-05-14","context-management-2025-06-27","prompt-caching-scope-2026-01-05","per-turn-control-2026-07-01","thinking-token-count-2026-05-13","mid-conversation-system-clear-at-2026-08-21","effort-2025-11-24","thinking-binding-controls-2026-08-01","thinking-display-updates-2026-08-18","cache-diagnosis-2026-04-07"],"max_tokens":128000,"thinking":{"type":"adaptive","display":"updates"},"context_management":{"edits":[{"type":"clear_thinking_20251015","keep":"all"}]},"output_config":{"effort":"medium"}},"base":"4fc8018d-77e5-4c00-b1a4-cf74be2bac2f","keep":6,"tail":["d6b468aaf8dbe3f7f52fc5039968d39408b7e44a3ea8f174b5999c3ec6d296a7","e7af6e07a35718b2de4f2ef99efb4fc16a0b920a4372c229e9d84a2241419c99"],"cacheControl":[{"path":["system",0],"value":{"type":"ephemeral"}},{"path":["system",1],"value":{"type":"ephemeral"}},{"path":["messages",7,"content",0],"value":{"type":"ephemeral"}}],"requestDigest":"e03c87377af885e3a6126e2b4f819db08e0c333e8f8b11f70777d445312c74ec"}35{"parentUuid":"1a1ed1e4-eb78-4b8f-8d86-718e922c46d6","isSidechain":false,"message":{"model":"claude-opus-5-5","id":"msg_011CgXsTfyJ8RS5869o1pUqE","type":"message","role":"assistant","content":[{"type":"tool_use","id":"toolu_015sT3AkPwt8kDmy57kxHaT1","name":"Bash","input":{"command":"cd out/state && cat > data_audit.md <<'EOF'\n# Data audit (P1)\n| file | SHA-256 | wc -l / items | matches README/bundle hash |\n|---|---|---|---|\n| data/assertions.json | 2965ab3acc6f326653169b83a5345698b51fac88a556de65faf89210aea0cad4 | 6 top-level items (fields id, cites, text) | yes (bundle) |\n| data/README.md | 5348bd49912099735108dbbe19ae09fa72bd600cb3d12b878658e6b9806198a7 | 14 lines | yes (bundle) |\n| data/sources/arxiv-2609.27732v1.txt | ee2d444d2f78f2af2ca2cf69b59a61fcd7ac5e10ea29e8ddcd67917bf07d6a8b | 134 lines | yes (README) |\n| data/sources/arxiv-2606.14621v1.txt | 27c463c0a144d9d5a3916dc641f15b6029f6c68b5e574ad9074e7df1aeb0a238 | 58 lines | yes (README) |\n\nNo duplicates among assertion ids (A1–A6); A1–A5 cite arxiv-2609.27732v1, A6 cites arxiv-2606.14621v1. No missing fields.\n\n## Anomalies / internal inconsistencies found in the sources\n1. DCR Table A19 prints the CS-DR 5 km ATT -0.431** with SE (0.218), while Table 6 prints the same estimate with SE (0.210).\n2. DCR Table A19 note says 640 never-treated comparison regions; Table A19 body, Table 6 and Figure 6 note say 608.\n3. DCR abstract says fatal hospitalisations \"fall by 35%\"; Table 7 5 km fatal ATT is -0.354 log points = -29.8%, and Section 6.1 says \"approximately 30%\". Abstract figure appears to read log points as percent.\n4. DCR text says HIV estimates are \"close to zero\", while Table 7 HIV at 3 km/5 km are -0.239/-0.340 (insignificant but not small).\n5. RESEA results text prints the weeks-on-UI CI as magnitudes \"[1.75 weeks, 2.24 weeks]\" while Table 2 prints signed [-2.24, -1.75] — consistent once sign convention is noted.\n6. RESEA line 39 rendering defect \"p ¡ 0.001\" (should be p < 0.001).\nNone of these violate the information-availability rules; all inputs are admissible. Handling: tables are treated as the primary locator; issues are recorded in results.json data_issues.\nEOF\nprintf 'step,rule,n_before,n_after,n_removed,rationale\\n0,none: all assertions assessed,6,6,0,No assertion excluded; every assertion cites a provided source\\n' > ../exclusions.csv\n~/wp29/venv/bin/python - <<'EOF'\nimport json;p=json.load(open('phases.json'))\np['P1']={\"status\":\"passed\",\"checks\":[\"SHA-256 computed and matched README/bundle for all 4 files\",\"line/item counts recorded\",\"anomalies listed (6)\",\"exclusions.csv written: 6 raw, 0 removed, 6 analysed\"],\"notes\":\"\"}\np['P2'][\"status\"]=\"running\"\njson.dump(p,open('phases.json','w'),indent=1)\nEOF\necho \"- 2026-10-30 P1 passed: audit done, 6 source anomalies recorded, no exclusions.\" >> log.md","description":"Write data audit and exclusions"},"caller":{"type":"direct"}}],"container":null,"stop_reason":"tool_use","stop_sequence":null,"stop_details":null,"usage":{"input_tokens":2,"cache_creation_input_tokens":2035,"cache_read_input_tokens":20838,"output_tokens":1274,"output_tokens_details":{"thinking_tokens":0},"server_tool_use":{"web_search_requests":0,"web_fetch_requests":0},"service_tier":"standard","cache_creation":{"ephemeral_1h_input_tokens":0,"ephemeral_5m_input_tokens":2035},"inference_geo":"global","iterations":[],"speed":"standard","fallback_credit":null},"input_transformations":[],"diagnostics":null,"context_management":null},"apiBlockIndex":0,"requestId":"req_011CgXsTfgw4qNi47mFu812j","requestRef":"6359c90a-6ae4-490c-a4d0-43b253880b80","requestedModel":"claude-opus-5-5","type":"assistant","uuid":"2b5f05d4-ec37-4c06-93e4-1ea96916df24","timestamp":"2026-10-30T05:29:37.964Z","effort":"medium","perTurnEffort":"medium","userType":"external","entrypoint":"sdk-cli","cwd":"/Users/simon-pierreboucher/wp29/runs/RC0094/out/state","sessionId":"989b99df-8772-4c22-b5b4-b743dc4be974","version":"2.1.314","gitBranch":"HEAD"}36{"parentUuid":"2b5f05d4-ec37-4c06-93e4-1ea96916df24","isSidechain":false,"promptId":"9ebd33b9-1875-4076-855f-328e8dae8857","type":"user","message":{"role":"user","content":[{"tool_use_id":"toolu_015sT3AkPwt8kDmy57kxHaT1","type":"tool_result","content":"(eval):cd:1: no such file or directory: out/state","is_error":false}]},"uuid":"aaf3a175-9671-420e-af54-d09fb6d89cf2","timestamp":"2026-10-30T05:29:38.009Z","toolUseResult":{"stdout":"(eval):cd:1: no such file or directory: out/state","stderr":"","interrupted":false,"isImage":false,"noOutputExpected":false},"sandboxed":false,"sourceToolAssistantUUID":"2b5f05d4-ec37-4c06-93e4-1ea96916df24","permissionDecision":{"decision":"accept","source":"config","reasonType":"rule","ruleSource":"cliArg"},"userType":"external","entrypoint":"sdk-cli","cwd":"/Users/simon-pierreboucher/wp29/runs/RC0094/out/state","sessionId":"989b99df-8772-4c22-b5b4-b743dc4be974","version":"2.1.314","gitBranch":"HEAD"}37{"type":"api-request-blob","sessionId":"989b99df-8772-4c22-b5b4-b743dc4be974","hash":"48389ffe9bd1ecc3e2f6be13344edb18f62ee9bc62f9fb29e98b309559617f85","message":{"role":"assistant","content":[{"type":"tool_use","id":"toolu_015sT3AkPwt8kDmy57kxHaT1","name":"Bash","input":{"command":"cd out/state && cat > data_audit.md <<'EOF'\n# Data audit (P1)\n| file | SHA-256 | wc -l / items | matches README/bundle hash |\n|---|---|---|---|\n| data/assertions.json | 2965ab3acc6f326653169b83a5345698b51fac88a556de65faf89210aea0cad4 | 6 top-level items (fields id, cites, text) | yes (bundle) |\n| data/README.md | 5348bd49912099735108dbbe19ae09fa72bd600cb3d12b878658e6b9806198a7 | 14 lines | yes (bundle) |\n| data/sources/arxiv-2609.27732v1.txt | ee2d444d2f78f2af2ca2cf69b59a61fcd7ac5e10ea29e8ddcd67917bf07d6a8b | 134 lines | yes (README) |\n| data/sources/arxiv-2606.14621v1.txt | 27c463c0a144d9d5a3916dc641f15b6029f6c68b5e574ad9074e7df1aeb0a238 | 58 lines | yes (README) |\n\nNo duplicates among assertion ids (A1–A6); A1–A5 cite arxiv-2609.27732v1, A6 cites arxiv-2606.14621v1. No missing fields.\n\n## Anomalies / internal inconsistencies found in the sources\n1. DCR Table A19 prints the CS-DR 5 km ATT -0.431** with SE (0.218), while Table 6 prints the same estimate with SE (0.210).\n2. DCR Table A19 note says 640 never-treated comparison regions; Table A19 body, Table 6 and Figure 6 note say 608.\n3. DCR abstract says fatal hospitalisations \"fall by 35%\"; Table 7 5 km fatal ATT is -0.354 log points = -29.8%, and Section 6.1 says \"approximately 30%\". Abstract figure appears to read log points as percent.\n4. DCR text says HIV estimates are \"close to zero\", while Table 7 HIV at 3 km/5 km are -0.239/-0.340 (insignificant but not small).\n5. RESEA results text prints the weeks-on-UI CI as magnitudes \"[1.75 weeks, 2.24 weeks]\" while Table 2 prints signed [-2.24, -1.75] — consistent once sign convention is noted.\n6. RESEA line 39 rendering defect \"p ¡ 0.001\" (should be p < 0.001).\nNone of these violate the information-availability rules; all inputs are admissible. 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> out/state/data_audit.md <<'EOF'\n# Data audit (P1)\n| file | SHA-256 | wc -l / items | matches README/bundle hash |\n|---|---|---|---|\n| data/assertions.json | 2965ab3acc6f326653169b83a5345698b51fac88a556de65faf89210aea0cad4 | 6 top-level items (fields id, cites, text) | yes (bundle) |\n| data/README.md | 5348bd49912099735108dbbe19ae09fa72bd600cb3d12b878658e6b9806198a7 | 14 lines | yes (bundle) |\n| data/sources/arxiv-2609.27732v1.txt | ee2d444d2f78f2af2ca2cf69b59a61fcd7ac5e10ea29e8ddcd67917bf07d6a8b | 134 lines | yes (README) |\n| data/sources/arxiv-2606.14621v1.txt | 27c463c0a144d9d5a3916dc641f15b6029f6c68b5e574ad9074e7df1aeb0a238 | 58 lines | yes (README) |\n\nNo duplicate assertion ids (A1–A6); A1–A5 cite arxiv-2609.27732v1, A6 cites arxiv-2606.14621v1. No missing fields. Units: DCR outcomes in log hospitalisation rates per 100,000 (ATTs in log points); RESEA weeks on UI in weeks.\n\n## Anomalies / internal inconsistencies found in the sources\n1. DCR Table A19 prints the CS-DR 5 km ATT -0.431** with SE (0.218), while Table 6 prints the same estimate with SE (0.210).\n2. DCR Table A19 note says 640 never-treated comparison regions; Table A19 body, Table 6 and Figure 6 note say 608.\n3. DCR abstract says fatal hospitalisations \"fall by 35%\"; Table 7 5 km fatal ATT is -0.354 log points = -29.8%, and Section 6.1 says \"approximately 30%\".\n4. DCR Section 6 text says HIV estimates are \"close to zero\", while Table 7 HIV at 3 km/5 km are -0.239/-0.340 (insignificant but not small).\n5. RESEA results text prints the weeks-on-UI CI as magnitudes \"[1.75 weeks, 2.24 weeks]\" while Table 2 prints signed [-2.24, -1.75] — consistent up to sign convention.\n6. RESEA line 39 rendering defect \"p ¡ 0.001\" (evidently p < 0.001).\nNone of these violate the information-availability rules; all inputs are admissible. 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every assertion cites a provided source\n- 2026-10-30 P0 passed: contract written.\n- 2026-10-30 P1 passed: audit done, 6 source anomalies recorded, no exclusions.\n{\n \"P0\": {\n \"status\": \"passed\",\n \"checks\": [\n \"TASK.md read fully\",","is_error":false}]},"uuid":"2ecdb3b8-e337-4d5b-963a-f95bd20d2056","timestamp":"2026-10-30T05:29:50.793Z","toolUseResult":{"stdout":"step,rule,n_before,n_after,n_removed,rationale\n0,none: all assertions assessed,6,6,0,No assertion excluded; every assertion cites a provided source\n- 2026-10-30 P0 passed: contract written.\n- 2026-10-30 P1 passed: audit done, 6 source anomalies recorded, no exclusions.\n{\n \"P0\": {\n \"status\": \"passed\",\n \"checks\": [\n \"TASK.md read fully\",","stderr":"","interrupted":false,"isImage":false,"noOutputExpected":false},"sandboxed":false,"sourceToolAssistantUUID":"ab3218e4-1bdd-4353-a3e3-bb1f7fa370e3","permissionDecision":{"decision":"accept","source":"config","reasonType":"rule","ruleSource":"cliArg"},"userType":"external","entrypoint":"sdk-cli","cwd":"/Users/simon-pierreboucher/wp29/runs/RC0094","sessionId":"989b99df-8772-4c22-b5b4-b743dc4be974","version":"2.1.314","gitBranch":"HEAD"}49{"type":"api-request-blob","sessionId":"989b99df-8772-4c22-b5b4-b743dc4be974","hash":"d665e5b469eba05640365b162c4413290ad392e0c934d2099132b4439fbaec89","message":{"role":"assistant","content":[{"type":"thinking","thinking":"","signature":"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"},{"type":"tool_use","id":"toolu_011EdcQ2uzA44GSFi2mGpisf","name":"Bash","input":{"command":"cat > out/state/data_audit.md <<'EOF'\n# Data audit (P1)\n| file | SHA-256 | wc -l / items | matches README/bundle hash |\n|---|---|---|---|\n| data/assertions.json | 2965ab3acc6f326653169b83a5345698b51fac88a556de65faf89210aea0cad4 | 6 top-level items (fields id, cites, text) | yes (bundle) |\n| data/README.md | 5348bd49912099735108dbbe19ae09fa72bd600cb3d12b878658e6b9806198a7 | 14 lines | yes (bundle) |\n| data/sources/arxiv-2609.27732v1.txt | ee2d444d2f78f2af2ca2cf69b59a61fcd7ac5e10ea29e8ddcd67917bf07d6a8b | 134 lines | yes (README) |\n| data/sources/arxiv-2606.14621v1.txt | 27c463c0a144d9d5a3916dc641f15b6029f6c68b5e574ad9074e7df1aeb0a238 | 58 lines | yes (README) |\n\nNo duplicate assertion ids (A1–A6); A1–A5 cite arxiv-2609.27732v1, A6 cites arxiv-2606.14621v1. No missing fields. Units: DCR outcomes in log hospitalisation rates per 100,000 (ATTs in log points); RESEA weeks on UI in weeks.\n\n## Anomalies / internal inconsistencies found in the sources\n1. DCR Table A19 prints the CS-DR 5 km ATT -0.431** with SE (0.218), while Table 6 prints the same estimate with SE (0.210).\n2. DCR Table A19 note says 640 never-treated comparison regions; Table A19 body, Table 6 and Figure 6 note say 608.\n3. DCR abstract says fatal hospitalisations \"fall by 35%\"; Table 7 5 km fatal ATT is -0.354 log points = -29.8%, and Section 6.1 says \"approximately 30%\".\n4. DCR Section 6 text says HIV estimates are \"close to zero\", while Table 7 HIV at 3 km/5 km are -0.239/-0.340 (insignificant but not small).\n5. RESEA results text prints the weeks-on-UI CI as magnitudes \"[1.75 weeks, 2.24 weeks]\" while Table 2 prints signed [-2.24, -1.75] — consistent up to sign convention.\n6. RESEA line 39 rendering defect \"p ¡ 0.001\" (evidently p < 0.001).\nNone of these violate the information-availability rules; all inputs are admissible. Handling: tables are treated as the primary locator; issues recorded in results.json data_issues.\nEOF\ncat out/exclusions.csv out/state/log.md; cat out/state/phases.json | head -5","description":"Write data audit file"}}]}}50{"type":"api-request","sessionId":"989b99df-8772-4c22-b5b4-b743dc4be974","id":"e4c9f69d-a692-486b-a717-aacc34502d1b","timestamp":"2026-10-30T05:29:50.797Z","version":"2.1.314","querySource":"sdk","shapeHash":"ca65346191cc3fbfd9b5075f5cd1e1d20265b723edff78ec161d4675b9c87931","params":{"model":"claude-opus-5-5","betas":["claude-code-20250219","interleaved-thinking-2025-05-14","context-management-2025-06-27","prompt-caching-scope-2026-01-05","per-turn-control-2026-07-01","thinking-token-count-2026-05-13","mid-conversation-system-clear-at-2026-08-21","effort-2025-11-24","thinking-binding-controls-2026-08-01","thinking-display-updates-2026-08-18","cache-diagnosis-2026-04-07"],"max_tokens":128000,"thinking":{"type":"adaptive","display":"updates"},"context_management":{"edits":[{"type":"clear_thinking_20251015","keep":"all"}]},"output_config":{"effort":"medium"}},"base":"70471ff5-8113-4f6f-81fa-bc8d8a5d947f","keep":12,"tail":["d665e5b469eba05640365b162c4413290ad392e0c934d2099132b4439fbaec89","bedc648874ed7bc65a1545f5f02e790d69d3c12b87a5b8dbc4a46963f1be75b4"],"cacheControl":[{"path":["system",0],"value":{"type":"ephemeral"}},{"path":["system",1],"value":{"type":"ephemeral"}},{"path":["messages",13,"content",0],"value":{"type":"ephemeral"}}],"requestDigest":"35d708d4a208911a7072f9246f1eab85a88bbd6aa02facb0b4d5f82d95e9788a"}51{"parentUuid":"2ecdb3b8-e337-4d5b-963a-f95bd20d2056","isSidechain":false,"message":{"model":"claude-opus-5-5","id":"msg_011CgXsVZ397CnWXYx5ZXHVv","type":"message","role":"assistant","content":[{"type":"thinking","thinking":"","signature":"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"}],"container":null,"stop_reason":"tool_use","stop_sequence":null,"stop_details":null,"usage":{"input_tokens":2,"cache_creation_input_tokens":1317,"cache_read_input_tokens":24402,"output_tokens":5484,"output_tokens_details":{"thinking_tokens":89},"server_tool_use":{"web_search_requests":0,"web_fetch_requests":0},"service_tier":"standard","cache_creation":{"ephemeral_1h_input_tokens":0,"ephemeral_5m_input_tokens":1317},"inference_geo":"global","iterations":[],"speed":"standard","fallback_credit":null},"input_transformations":[],"diagnostics":null,"context_management":null},"thinkingDurationMs":1128,"thinkingDisplay":"updates","apiBlockIndex":0,"requestId":"req_011CgXsVYm1rcusvzyD82jCd","requestRef":"e4c9f69d-a692-486b-a717-aacc34502d1b","requestedModel":"claude-opus-5-5","type":"assistant","uuid":"c5641a9e-05a3-451e-8413-9c36c7d67d08","timestamp":"2026-10-30T05:29:53.094Z","effort":"medium","perTurnEffort":"medium","userType":"external","entrypoint":"sdk-cli","cwd":"/Users/simon-pierreboucher/wp29/runs/RC0094","sessionId":"989b99df-8772-4c22-b5b4-b743dc4be974","version":"2.1.314","gitBranch":"HEAD"}52{"parentUuid":"c5641a9e-05a3-451e-8413-9c36c7d67d08","isSidechain":false,"message":{"model":"claude-opus-5-5","id":"msg_011CgXsVZ397CnWXYx5ZXHVv","type":"message","role":"assistant","content":[{"type":"tool_use","id":"toolu_01Q53Q1ym3eAaHVyWrApqjNv","name":"Bash","input":{"command":"cat > out/analysis.py <<'EOF'\n\"\"\"F4-conf-02: verify six assertions against cited source extracts.\nReads only data/; writes out/results.json deterministically (no randomness).\"\"\"\nimport json, math, os, re\n\nROOT = os.path.dirname(os.path.dirname(os.path.abspath(__file__)))\nD = os.path.join(ROOT, \"data\")\nOUT = os.path.join(ROOT, \"out\")\n\ndef lines_of(p):\n with open(p, encoding=\"utf-8\") as f:\n return f.read().split(\"\\n\")\n\ndef wc_l(p):\n with open(p, \"rb\") as f:\n return f.read().count(b\"\\n\")\n\nassertions = json.load(open(os.path.join(D, \"assertions.json\"), encoding=\"utf-8\"))\nA = {a[\"id\"]: a for a in assertions}\nDCR, RES = \"arxiv-2609.27732v1\", \"arxiv-2606.14621v1\"\nsrc = {s: lines_of(os.path.join(D, \"sources\", s + \".txt\")) for s in (DCR, RES)}\n\ndef find(sid, pattern, start=0):\n \"\"\"Return (line_no, text) of first line at/after `start` matching regex.\"\"\"\n for i, l in enumerate(src[sid][start:], start=start):\n if re.search(pattern, l):\n return i + 1, l\n raise ValueError(f\"pattern {pattern!r} not found in {sid}\")\n\ndef show(tag, sid, ln, txt):\n print(f\"[{tag}] {sid}:{ln}: {txt.strip()}\")\n\ndef nums(s):\n return [float(x.replace(\",\", \"\")) for x in re.findall(r\"-?\\d[\\d,]*\\.?\\d*\", s)]\n\ndef cells(line):\n return [c.strip() for c in line.split(\"|\")]\n\ndef coef(c): # '-0.431**' -> -0.431\n return float(re.sub(r\"[*%]\", \"\", c))\n\ndef pct(b):\n return 100 * (math.exp(b) - 1)\n\ndef ci(b, se, z):\n return (b - z * se, b + z * se)\n\n# ---------- locate tables in DCR source ----------\nt6, _ = find(DCR, r\"^Table 6:\")\nln_att6, l_att6 = find(DCR, r\"^ATT \\|\", t6)\nln_se6, l_se6 = ln_att6 + 2, src[DCR][ln_att6 + 1]\nln_pc6, l_pc6 = find(DCR, r\"^% change \\|\", t6)\natt6 = [coef(c) for c in cells(l_att6)[1:]] # 1,3,5 km\nse6 = [float(c.strip(\"()\")) for c in cells(l_se6)[1:]]\npc6 = [coef(c) for c in cells(l_pc6)[1:]]\nstars6 = [c.count(\"*\") for c in cells(l_att6)[1:]]\n\nt7, _ = find(DCR, r\"^Table 7:\")\ndef t7row(name):\n ln, l = find(DCR, r\"^\" + re.escape(name) + r\" \\|\", t7)\n se_l = src[DCR][ln] # next-but-blank line holds SE (line ln+2 in 1-based)\n se_l = src[DCR][ln + 1]\n return ln, l, ln + 2, se_l, [coef(c) for c in cells(l)[1:]], [float(c.strip(\"()\")) for c in cells(se_l)[1:]]\nhiv = t7row(\"HIV\")\nhep = t7row(\"Hepatitis\")\n\nta19, _ = find(DCR, r\"^Table A19:\")\nln_a19, l_a19 = find(DCR, r\"^ATT \\|\", ta19)\nl_a19se = src[DCR][ln_a19 + 1]\nln_a19note, l_a19note = find(DCR, r\"never-treated comparison regions\", ta19)\n\nprint(\"=== Source lines relied on ===\")\nfor a in assertions:\n print(f\"{a['id']} (cites {a['cites']}): {a['text']}\")\nprint()\n\nverdicts, locators, reasons, details = {}, {}, {}, {}\n\n# ---------- A1 ----------\nshow(\"A1\", DCR, ln_att6, l_att6); show(\"A1\", DCR, ln_se6, l_se6); show(\"A1\", DCR, ln_pc6, l_pc6)\nb, se, st, p = att6[2], se6[2], stars6[2], pc6[2]\nok = (b == -0.431 and se == 0.210 and st == 2 and p == -35.0 and round(pct(b), 1) == -35.0\n and abs(b / se) > 1.96)\ndetails[\"A1\"] = {\"att\": b, \"se\": se, \"stars\": st, \"printed_pct\": p, \"computed_pct\": round(pct(b), 2),\n \"z\": round(b / se, 3)}\nverdicts[\"A1\"] = \"supported\" if ok else \"not_supported\"\nlocators[\"A1\"] = f'{DCR} | Table 6 | row \"ATT\" | column \"5 km\"'\nreasons[\"A1\"] = (\"Table 6 prints the 5 km ATT as -0.431** with SE (0.210) and % change -35.0% \"\n \"(100*(exp(-0.431)-1) = -35.0%), so estimate, SE, 5% significance and the 35.0% reduction all match.\")\n\n# ---------- A2 ----------\nshow(\"A2\", DCR, hiv[0], hiv[1]); show(\"A2\", DCR, hiv[2], hiv[3])\nb1 = hiv[4][0]\ndetails[\"A2\"] = {\"hiv_att_1km\": b1, \"hiv_se_1km\": hiv[5][0], \"asserted\": -0.063}\nverdicts[\"A2\"] = \"supported\" if b1 < 0 else \"not_supported\"\nlocators[\"A2\"] = f'{DCR} | Table 7 | row \"HIV\" | column \"1 km\"'\nreasons[\"A2\"] = (\"Table 7 prints the 1 km HIV ATT as +0.063 (SE 0.801), so the asserted negative sign \"\n \"(-0.063) and the claimed fall in HIV hospitalisations are contradicted.\")\n\n# ---------- A3 ----------\nshow(\"A3\", DCR, ln_att6, l_att6); show(\"A3\", DCR, ln_pc6, l_pc6)\nb3, p3 = att6[1], pc6[1]\ndetails[\"A3\"] = {\"att_3km\": b3, \"printed_pct_3km\": p3, \"computed_pct_3km\": round(pct(b3), 2), \"asserted_pct\": -28.3}\nverdicts[\"A3\"] = \"supported\" if abs(p3 - (-28.3)) < 0.05 else \"not_supported\"\nlocators[\"A3\"] = f'{DCR} | Table 6 | row \"% change\" | column \"3 km\"'\nreasons[\"A3\"] = (\"Table 6 converts the 3 km ATT of -0.283 to a -24.7% change (100*(exp(-0.283)-1) = -24.7%), \"\n \"so the asserted 28.3% reduction wrongly reads log points as percent.\")\n\n# ---------- A4 ----------\nshow(\"A4\", DCR, hep[0], hep[1]); show(\"A4\", DCR, hep[2], hep[3])\nb4, se4 = hep[4][2], hep[5][2]\nc196, c200, c1 = ci(b4, se4, 1.96), ci(b4, se4, 2.0), ci(b4, se4, 1.0)\nexcl196 = c196[0] > 0 or c196[1] < 0\nexcl200 = c200[0] > 0 or c200[1] < 0\ndetails[\"A4\"] = {\"att_5km\": b4, \"se_5km\": se4, \"ci95_z1.96\": [round(x, 3) for x in c196],\n \"ci95_z2.0\": [round(x, 3) for x in c200], \"pm_1se\": [round(x, 3) for x in c1],\n \"excludes_zero_z1.96\": excl196, \"excludes_zero_z2.0\": excl200,\n \"stars_printed\": hep[1].split(\"|\")[3].count(\"*\")}\nverdicts[\"A4\"] = \"supported\" if (excl196 and abs(c196[0] + 0.66) < 0.03 and abs(c196[1] + 0.16) < 0.03) else \"not_supported\"\nlocators[\"A4\"] = f'{DCR} | Table 7 | row \"Hepatitis\" | column \"5 km\"'\nreasons[\"A4\"] = (f\"Table 7 prints the 5 km hepatitis ATT as -0.406 (SE 0.250) with no star, giving a 95% CI of \"\n f\"[{c196[0]:.3f}, {c196[1]:.3f}] that includes zero; the asserted [-0.66, -0.16] is only +/-1 SE.\")\n\n# ---------- A5 ----------\nsex_hits = [(i + 1, l) for i, l in enumerate(src[DCR])\n if re.search(r\"\\b(men|women|male|female|sex|gender)\\b\", l, re.I)]\nprint(f\"[A5] lines in {DCR} mentioning men/women/male/female/sex/gender: {len(sex_hits)}\")\nfor ln, l in sex_hits:\n show(\"A5\", DCR, ln, l)\ndetails[\"A5\"] = {\"n_lines_mentioning_sex_or_gender\": len(sex_hits)}\nverdicts[\"A5\"] = \"not_assessable\" if not sex_hits else \"REVIEW\"\nlocators[\"A5\"] = f\"not reported in {DCR}\"\nreasons[\"A5\"] = (\"The extract reports ATTs only by buffer (Table 6) and diagnostic category (Table 7, Table A19) \"\n \"and contains no estimate by sex, so the men-versus-women comparison can be neither confirmed nor refuted.\")\n\n# ---------- A6 ----------\nln6, l6 = find(RES, r\"^Weeks on UI \\|\")\nshow(\"A6\", RES, ln6, l6)\nln6t, l6t = find(RES, r\"11\\.5% decrease\")\nshow(\"A6\", RES, ln6t, l6t[:0] + \"...a 1.99 week reduction in the number of weeks on UI (95% CI: [1.75 weeks, 2.24 weeks]; p<0.001) ... 11.5% decrease compared to the mean control group weeks on UI outcome of 17.3 weeks.\")\nc = cells(l6)\nate = c[4]; ctrl = c[2]\nate_n = nums(ate)\nctrl_mean = nums(ctrl)[0]\nest, lo, hi = ate_n[0], ate_n[-2], ate_n[-1]\nrel = 100 * est / ctrl_mean\ndetails[\"A6\"] = {\"ate\": est, \"ci95\": [lo, hi], \"control_mean\": ctrl_mean, \"computed_rel_pct\": round(rel, 2)}\nok6 = est == -1.99 and lo == -2.24 and hi == -1.75 and ctrl_mean == 17.3 and round(rel, 1) == -11.5\nverdicts[\"A6\"] = \"supported\" if ok6 else \"not_supported\"\nlocators[\"A6\"] = f'{RES} | Table 2 | row \"Weeks on UI\" | column \"Average treatment effect estimate\"'\nreasons[\"A6\"] = (\"Table 2 prints the ATE as -1.99 weeks with 95% CI [-2.24, -1.75] and a control mean of 17.3 weeks, \"\n \"and -1.99/17.3 = -11.5%, matching the text's 11.5% decrease.\")\n\n# ---------- naive baseline: do all numbers in the assertion appear verbatim in the cited source? ----------\nbaseline = {}\nfor a in assertions:\n text = src[a[\"cites\"]]\n blob = \"\\n\".join(text).replace(\"−\", \"-\")\n toks = re.findall(r\"\\d+(?:\\.\\d+)?\", a[\"text\"].replace(\"−\", \"-\"))\n toks = [t for t in toks if t not in (\"1\", \"3\", \"5\", \"95\")]\n baseline[a[\"id\"]] = all(t in blob for t in toks)\nprint(\"\\nNaive baseline (all numbers verbatim in source):\", baseline)\n\ndata_issues = [\n {\"issue\": f\"{DCR}: Table A19 prints the CS-DR 5 km ATT -0.431** with SE (0.218), whereas Table 6 prints the same estimate with SE (0.210).\",\n \"handling\": \"Table 6 (the main results table, the one A1 cites) is used as the locator for A1; A1's 5% significance also holds with SE 0.218 at z=1.96 (|t|=1.98), and the source prints ** in both tables.\"},\n {\"issue\": f\"{DCR}: Table A19 note says 640 never-treated comparison regions, while Table A19 body, Table 6 and the Figure 6 note say 608.\",\n \"handling\": \"Recorded only; no assertion depends on the control-region count.\"},\n {\"issue\": f\"{DCR}: abstract states fatal hospitalisations fall by 35%, but Table 7 5 km fatal ATT -0.354 implies -29.8% and Section 6.1 says approximately 30%.\",\n \"handling\": \"Recorded only; no assertion concerns fatal hospitalisations. Tables are treated as primary evidence.\"},\n {\"issue\": f\"{DCR}: Section 6 text calls HIV estimates 'close to zero' although Table 7 HIV ATTs at 3 km/5 km are -0.239/-0.340 (insignificant).\",\n \"handling\": \"A2 is decided by the Table 7 1 km cell (+0.063), not by the narrative.\"},\n {\"issue\": f\"{RES}: results text gives the weeks-on-UI CI as unsigned magnitudes [1.75 weeks, 2.24 weeks] while Table 2 prints the signed CI [-2.24, -1.75].\",\n \"handling\": \"Treated as the same interval expressed as a reduction; A6 is decided by Table 2.\"},\n {\"issue\": f\"{RES}: rendering defect 'p ¡ 0.001' in the short-term weeks-on-UI sentence.\",\n \"handling\": \"Read as p < 0.001 (consistent with Table 2); not decisive for any assertion.\"},\n]\n\nn_input_rows = {\"assertions.json\": len(assertions), \"README.md\": wc_l(os.path.join(D, \"README.md\"))}\nfor s in (DCR, RES):\n n_input_rows[s + \".txt\"] = wc_l(os.path.join(D, \"sources\", s + \".txt\"))\n\nvals = list(verdicts.values())\nresults = {\n \"task_id\": \"F4-conf-02\",\n \"verdicts\": verdicts,\n \"locators\": locators,\n \"reasons\": reasons,\n \"n_supported\": vals.count(\"supported\"),\n \"n_not_supported\": vals.count(\"not_supported\"),\n \"n_not_assessable\": vals.count(\"not_assessable\"),\n \"feasibility\": \"complete\",\n \"feasibility_reason\": None,\n \"data_issues\": data_issues,\n \"n_input_rows\": n_input_rows,\n \"n_analysed\": len(assertions),\n \"random_seed\": None,\n \"baseline_numeric_verbatim_match\": baseline,\n \"computation_details\": details,\n}\nos.makedirs(OUT, exist_ok=True)\nwith open(os.path.join(OUT, \"results.json\"), \"w\", encoding=\"utf-8\") as f:\n json.dump(results, f, indent=2, ensure_ascii=False)\nprint(\"\\nVerdicts:\", verdicts)\nprint(\"Counts: supported=%d not_supported=%d not_assessable=%d\" %\n (results[\"n_supported\"], results[\"n_not_supported\"], results[\"n_not_assessable\"]))\nEOF\n~/wp29/venv/bin/python out/analysis.py && cat out/results.json | head -80","description":"Write and run analysis script"},"caller":{"type":"direct"}}],"container":null,"stop_reason":"tool_use","stop_sequence":null,"stop_details":null,"usage":{"input_tokens":2,"cache_creation_input_tokens":1317,"cache_read_input_tokens":24402,"output_tokens":5484,"output_tokens_details":{"thinking_tokens":89},"server_tool_use":{"web_search_requests":0,"web_fetch_requests":0},"service_tier":"standard","cache_creation":{"ephemeral_1h_input_tokens":0,"ephemeral_5m_input_tokens":1317},"inference_geo":"global","iterations":[],"speed":"standard","fallback_credit":null},"input_transformations":[],"diagnostics":null,"context_management":null},"apiBlockIndex":1,"requestId":"req_011CgXsVYm1rcusvzyD82jCd","requestRef":"e4c9f69d-a692-486b-a717-aacc34502d1b","requestedModel":"claude-opus-5-5","type":"assistant","uuid":"5c8576ac-172c-4d9a-a754-f97b7a078d3f","timestamp":"2026-10-30T05:30:33.062Z","effort":"medium","perTurnEffort":"medium","userType":"external","entrypoint":"sdk-cli","cwd":"/Users/simon-pierreboucher/wp29/runs/RC0094","sessionId":"989b99df-8772-4c22-b5b4-b743dc4be974","version":"2.1.314","gitBranch":"HEAD"}53{"parentUuid":"5c8576ac-172c-4d9a-a754-f97b7a078d3f","isSidechain":false,"promptId":"9ebd33b9-1875-4076-855f-328e8dae8857","type":"user","message":{"role":"user","content":[{"tool_use_id":"toolu_01Q53Q1ym3eAaHVyWrApqjNv","type":"tool_result","content":"=== Source lines relied on ===\nA1 (cites arxiv-2609.27732v1): Within 5 km of a drug consumption room, the overall ATT on the log drug-related hospitalisation rate is −0.431 (SE 0.210), statistically significant at the 5% level, which corresponds to a 35.0% reduction in the hospitalisation rate.\nA2 (cites arxiv-2609.27732v1): At the 1 km buffer, the estimated ATT for HIV hospitalisations is negative (−0.063), i.e. HIV hospitalisations fall after a DCR opening in the immediate vicinity.\nA3 (cites arxiv-2609.27732v1): The 3 km ATT of −0.283 implies a 28.3% reduction in drug-related hospitalisations within 3 km of a DCR.\nA4 (cites arxiv-2609.27732v1): For viral hepatitis at the 5 km buffer, the 95% confidence interval of the ATT is approximately [−0.66, −0.16] and therefore excludes zero.\nA5 (cites arxiv-2609.27732v1): The reduction in drug-related hospitalisations after a DCR opening is larger for men than for women.\nA6 (cites arxiv-2606.14621v1): Selection into RESEA reduced the number of weeks on UI by 1.99 weeks (95% CI [−2.24, −1.75]), an 11.5% decrease relative to the control-group mean of 17.3 weeks.\n\n[A1] arxiv-2609.27732v1:36: ATT | -0.399 | -0.283 | -0.431**\n[A1] arxiv-2609.27732v1:38: | (0.412) | (0.279) | (0.210)\n[A1] arxiv-2609.27732v1:40: % change | -32.9% | -24.7% | -35.0%\n[A2] arxiv-2609.27732v1:78: HIV | 0.063 | -0.239 | -0.340\n[A2] arxiv-2609.27732v1:80: | (0.801) | (0.337) | (0.294)\n[A3] arxiv-2609.27732v1:36: ATT | -0.399 | -0.283 | -0.431**\n[A3] arxiv-2609.27732v1:40: % change | -32.9% | -24.7% | -35.0%\n[A4] arxiv-2609.27732v1:74: Hepatitis | -0.270 | -0.413 | -0.406\n[A4] arxiv-2609.27732v1:76: | (0.486) | (0.270) | (0.250)\n[A5] lines in arxiv-2609.27732v1 mentioning men/women/male/female/sex/gender: 0\n[A6] arxiv-2606.14621v1:30: Weeks on UI | 15.2 weeks (SD: 9.3) | 17.3 weeks (SD: 9.4) | -2.10 weeks; p<0.001; 95% CI: [-2.34, -1.86] | -1.99 weeks; p<0.001; 95% CI: [-2.24, -1.75]\n[A6] arxiv-2606.14621v1:37: ...a 1.99 week reduction in the number of weeks on UI (95% CI: [1.75 weeks, 2.24 weeks]; p<0.001) ... 11.5% decrease compared to the mean control group weeks on UI outcome of 17.3 weeks.\n\nNaive baseline (all numbers verbatim in source): {'A1': True, 'A2': True, 'A3': False, 'A4': False, 'A5': True, 'A6': True}\n\nVerdicts: {'A1': 'supported', 'A2': 'not_supported', 'A3': 'not_supported', 'A4': 'not_supported', 'A5': 'not_assessable', 'A6': 'supported'}\nCounts: supported=2 not_supported=3 not_assessable=1\n{\n \"task_id\": \"F4-conf-02\",\n \"verdicts\": {\n \"A1\": \"supported\",\n \"A2\": \"not_supported\",\n \"A3\": \"not_supported\",\n \"A4\": \"not_supported\",\n \"A5\": \"not_assessable\",\n \"A6\": \"supported\"\n },\n \"locators\": {\n \"A1\": \"arxiv-2609.27732v1 | Table 6 | row \\\"ATT\\\" | column \\\"5 km\\\"\",\n \"A2\": \"arxiv-2609.27732v1 | Table 7 | row \\\"HIV\\\" | column \\\"1 km\\\"\",\n \"A3\": \"arxiv-2609.27732v1 | Table 6 | row \\\"% change\\\" | column \\\"3 km\\\"\",\n \"A4\": \"arxiv-2609.27732v1 | Table 7 | row \\\"Hepatitis\\\" | column \\\"5 km\\\"\",\n \"A5\": \"not reported in arxiv-2609.27732v1\",\n \"A6\": \"arxiv-2606.14621v1 | Table 2 | row \\\"Weeks on UI\\\" | column \\\"Average treatment effect estimate\\\"\"\n },\n \"reasons\": {\n \"A1\": \"Table 6 prints the 5 km ATT as -0.431** with SE (0.210) and % change -35.0% (100*(exp(-0.431)-1) = -35.0%), so estimate, SE, 5% significance and the 35.0% reduction all match.\",\n \"A2\": \"Table 7 prints the 1 km HIV ATT as +0.063 (SE 0.801), so the asserted negative sign (-0.063) and the claimed fall in HIV hospitalisations are contradicted.\",\n \"A3\": \"Table 6 converts the 3 km ATT of -0.283 to a -24.7% change (100*(exp(-0.283)-1) = -24.7%), so the asserted 28.3% reduction wrongly reads log points as percent.\",\n \"A4\": \"Table 7 prints the 5 km hepatitis ATT as -0.406 (SE 0.250) with no star, giving a 95% CI of [-0.896, 0.084] that includes zero; the asserted [-0.66, -0.16] is only +/-1 SE.\",\n \"A5\": \"The extract reports ATTs only by buffer (Table 6) and diagnostic category (Table 7, Table A19) and contains no estimate by sex, so the men-versus-women comparison can be neither confirmed nor refuted.\",\n \"A6\": \"Table 2 prints the ATE as -1.99 weeks with 95% CI [-2.24, -1.75] and a control mean of 17.3 weeks, and -1.99/17.3 = -11.5%, matching the text's 11.5% decrease.\"\n },\n \"n_supported\": 2,\n \"n_not_supported\": 3,\n \"n_not_assessable\": 1,\n \"feasibility\": \"complete\",\n \"feasibility_reason\": null,\n \"data_issues\": [\n {\n \"issue\": \"arxiv-2609.27732v1: Table A19 prints the CS-DR 5 km ATT -0.431** with SE (0.218), whereas Table 6 prints the same estimate with SE (0.210).\",\n \"handling\": \"Table 6 (the main results table, the one A1 cites) is used as the locator for A1; A1's 5% significance also holds with SE 0.218 at z=1.96 (|t|=1.98), and the source prints ** in both tables.\"\n },\n {\n \"issue\": \"arxiv-2609.27732v1: Table A19 note says 640 never-treated comparison regions, while Table A19 body, Table 6 and the Figure 6 note say 608.\",\n \"handling\": \"Recorded only; no assertion depends on the control-region count.\"\n },\n {\n \"issue\": \"arxiv-2609.27732v1: abstract states fatal hospitalisations fall by 35%, but Table 7 5 km fatal ATT -0.354 implies -29.8% and Section 6.1 says approximately 30%.\",\n \"handling\": \"Recorded only; no assertion concerns fatal hospitalisations. Tables are treated as primary evidence.\"\n },\n {\n \"issue\": \"arxiv-2609.27732v1: Section 6 text calls HIV estimates 'close to zero' although Table 7 HIV ATTs at 3 km/5 km are -0.239/-0.340 (insignificant).\",\n \"handling\": \"A2 is decided by the Table 7 1 km cell (+0.063), not by the narrative.\"\n },\n {\n \"issue\": \"arxiv-2606.14621v1: results text gives the weeks-on-UI CI as unsigned magnitudes [1.75 weeks, 2.24 weeks] while Table 2 prints the signed CI [-2.24, -1.75].\",\n \"handling\": \"Treated as the same interval expressed as a reduction; A6 is decided by Table 2.\"\n },\n {\n \"issue\": \"arxiv-2606.14621v1: rendering defect 'p ¡ 0.001' in the short-term weeks-on-UI sentence.\",\n \"handling\": \"Read as p < 0.001 (consistent with Table 2); not decisive for any assertion.\"\n }\n ],\n \"n_input_rows\": {\n \"assertions.json\": 6,\n \"README.md\": 14,\n \"arxiv-2609.27732v1.txt\": 134,\n \"arxiv-2606.14621v1.txt\": 58\n },\n \"n_analysed\": 6,\n \"random_seed\": null,\n \"baseline_numeric_verbatim_match\": {\n \"A1\": true,\n \"A2\": true,\n \"A3\": false,\n \"A4\": false,\n \"A5\": true,\n \"A6\": true\n },\n \"computation_details\": {\n \"A1\": {\n \"att\": -0.431,\n \"se\": 0.21,\n \"stars\": 2,\n \"printed_pct\": -35.0,\n \"computed_pct\": -35.01,","is_error":false}]},"uuid":"d41b6824-4798-406d-b080-a7b6da2cd0ab","timestamp":"2026-10-30T05:30:33.116Z","toolUseResult":{"stdout":"=== Source lines relied on ===\nA1 (cites arxiv-2609.27732v1): Within 5 km of a drug consumption room, the overall ATT on the log drug-related hospitalisation rate is −0.431 (SE 0.210), statistically significant at the 5% level, which corresponds to a 35.0% reduction in the hospitalisation rate.\nA2 (cites arxiv-2609.27732v1): At the 1 km buffer, the estimated ATT for HIV hospitalisations is negative (−0.063), i.e. HIV hospitalisations fall after a DCR opening in the immediate vicinity.\nA3 (cites arxiv-2609.27732v1): The 3 km ATT of −0.283 implies a 28.3% reduction in drug-related hospitalisations within 3 km of a DCR.\nA4 (cites arxiv-2609.27732v1): For viral hepatitis at the 5 km buffer, the 95% confidence interval of the ATT is approximately [−0.66, −0.16] and therefore excludes zero.\nA5 (cites arxiv-2609.27732v1): The reduction in drug-related hospitalisations after a DCR opening is larger for men than for women.\nA6 (cites arxiv-2606.14621v1): Selection into RESEA reduced the number of weeks on UI by 1.99 weeks (95% CI [−2.24, −1.75]), an 11.5% decrease relative to the control-group mean of 17.3 weeks.\n\n[A1] arxiv-2609.27732v1:36: ATT | -0.399 | -0.283 | -0.431**\n[A1] arxiv-2609.27732v1:38: | (0.412) | (0.279) | (0.210)\n[A1] arxiv-2609.27732v1:40: % change | -32.9% | -24.7% | -35.0%\n[A2] arxiv-2609.27732v1:78: HIV | 0.063 | -0.239 | -0.340\n[A2] arxiv-2609.27732v1:80: | (0.801) | (0.337) | (0.294)\n[A3] arxiv-2609.27732v1:36: ATT | -0.399 | -0.283 | -0.431**\n[A3] arxiv-2609.27732v1:40: % change | -32.9% | -24.7% | -35.0%\n[A4] arxiv-2609.27732v1:74: Hepatitis | -0.270 | -0.413 | -0.406\n[A4] arxiv-2609.27732v1:76: | (0.486) | (0.270) | (0.250)\n[A5] lines in arxiv-2609.27732v1 mentioning men/women/male/female/sex/gender: 0\n[A6] arxiv-2606.14621v1:30: Weeks on UI | 15.2 weeks (SD: 9.3) | 17.3 weeks (SD: 9.4) | -2.10 weeks; p<0.001; 95% CI: [-2.34, -1.86] | -1.99 weeks; p<0.001; 95% CI: [-2.24, -1.75]\n[A6] arxiv-2606.14621v1:37: ...a 1.99 week reduction in the number of weeks on UI (95% CI: [1.75 weeks, 2.24 weeks]; p<0.001) ... 11.5% decrease compared to the mean control group weeks on UI outcome of 17.3 weeks.\n\nNaive baseline (all numbers verbatim in source): {'A1': True, 'A2': True, 'A3': False, 'A4': False, 'A5': True, 'A6': True}\n\nVerdicts: {'A1': 'supported', 'A2': 'not_supported', 'A3': 'not_supported', 'A4': 'not_supported', 'A5': 'not_assessable', 'A6': 'supported'}\nCounts: supported=2 not_supported=3 not_assessable=1\n{\n \"task_id\": \"F4-conf-02\",\n \"verdicts\": {\n \"A1\": \"supported\",\n \"A2\": \"not_supported\",\n \"A3\": \"not_supported\",\n \"A4\": \"not_supported\",\n \"A5\": \"not_assessable\",\n \"A6\": \"supported\"\n },\n \"locators\": {\n \"A1\": \"arxiv-2609.27732v1 | Table 6 | row \\\"ATT\\\" | column \\\"5 km\\\"\",\n \"A2\": \"arxiv-2609.27732v1 | Table 7 | row \\\"HIV\\\" | column \\\"1 km\\\"\",\n \"A3\": \"arxiv-2609.27732v1 | Table 6 | row \\\"% change\\\" | column \\\"3 km\\\"\",\n \"A4\": \"arxiv-2609.27732v1 | Table 7 | row \\\"Hepatitis\\\" | column \\\"5 km\\\"\",\n \"A5\": \"not reported in arxiv-2609.27732v1\",\n \"A6\": \"arxiv-2606.14621v1 | Table 2 | row \\\"Weeks on UI\\\" | column \\\"Average treatment effect estimate\\\"\"\n },\n \"reasons\": {\n \"A1\": \"Table 6 prints the 5 km ATT as -0.431** with SE (0.210) and % change -35.0% (100*(exp(-0.431)-1) = -35.0%), so estimate, SE, 5% significance and the 35.0% reduction all match.\",\n \"A2\": \"Table 7 prints the 1 km HIV ATT as +0.063 (SE 0.801), so the asserted negative sign (-0.063) and the claimed fall in HIV hospitalisations are contradicted.\",\n \"A3\": \"Table 6 converts the 3 km ATT of -0.283 to a -24.7% change (100*(exp(-0.283)-1) = -24.7%), so the asserted 28.3% reduction wrongly reads log points as percent.\",\n \"A4\": \"Table 7 prints the 5 km hepatitis ATT as -0.406 (SE 0.250) with no star, giving a 95% CI of [-0.896, 0.084] that includes zero; the asserted [-0.66, -0.16] is only +/-1 SE.\",\n \"A5\": \"The extract reports ATTs only by buffer (Table 6) and diagnostic category (Table 7, Table A19) and contains no estimate by sex, so the men-versus-women comparison can be neither confirmed nor refuted.\",\n \"A6\": \"Table 2 prints the ATE as -1.99 weeks with 95% CI [-2.24, -1.75] and a control mean of 17.3 weeks, and -1.99/17.3 = -11.5%, matching the text's 11.5% decrease.\"\n },\n \"n_supported\": 2,\n \"n_not_supported\": 3,\n \"n_not_assessable\": 1,\n \"feasibility\": \"complete\",\n \"feasibility_reason\": null,\n \"data_issues\": [\n {\n \"issue\": \"arxiv-2609.27732v1: Table A19 prints the CS-DR 5 km ATT -0.431** with SE (0.218), whereas Table 6 prints the same estimate with SE (0.210).\",\n \"handling\": \"Table 6 (the main results table, the one A1 cites) is used as the locator for A1; A1's 5% significance also holds with SE 0.218 at z=1.96 (|t|=1.98), and the source prints ** in both tables.\"\n },\n {\n \"issue\": \"arxiv-2609.27732v1: Table A19 note says 640 never-treated comparison regions, while Table A19 body, Table 6 and the Figure 6 note say 608.\",\n \"handling\": \"Recorded only; no assertion depends on the control-region count.\"\n },\n {\n \"issue\": \"arxiv-2609.27732v1: abstract states fatal hospitalisations fall by 35%, but Table 7 5 km fatal ATT -0.354 implies -29.8% and Section 6.1 says approximately 30%.\",\n \"handling\": \"Recorded only; no assertion concerns fatal hospitalisations. Tables are treated as primary evidence.\"\n },\n {\n \"issue\": \"arxiv-2609.27732v1: Section 6 text calls HIV estimates 'close to zero' although Table 7 HIV ATTs at 3 km/5 km are -0.239/-0.340 (insignificant).\",\n \"handling\": \"A2 is decided by the Table 7 1 km cell (+0.063), not by the narrative.\"\n },\n {\n \"issue\": \"arxiv-2606.14621v1: results text gives the weeks-on-UI CI as unsigned magnitudes [1.75 weeks, 2.24 weeks] while Table 2 prints the signed CI [-2.24, -1.75].\",\n \"handling\": \"Treated as the same interval expressed as a reduction; A6 is decided by Table 2.\"\n },\n {\n \"issue\": \"arxiv-2606.14621v1: rendering defect 'p ¡ 0.001' in the short-term weeks-on-UI sentence.\",\n \"handling\": \"Read as p < 0.001 (consistent with Table 2); not decisive for any assertion.\"\n }\n ],\n \"n_input_rows\": {\n \"assertions.json\": 6,\n \"README.md\": 14,\n \"arxiv-2609.27732v1.txt\": 134,\n \"arxiv-2606.14621v1.txt\": 58\n },\n \"n_analysed\": 6,\n \"random_seed\": null,\n \"baseline_numeric_verbatim_match\": {\n \"A1\": true,\n \"A2\": true,\n \"A3\": false,\n \"A4\": false,\n \"A5\": true,\n \"A6\": true\n },\n \"computation_details\": {\n \"A1\": {\n \"att\": -0.431,\n \"se\": 0.21,\n \"stars\": 2,\n \"printed_pct\": -35.0,\n \"computed_pct\": -35.01,","stderr":"","interrupted":false,"isImage":false,"noOutputExpected":false},"sandboxed":false,"sourceToolAssistantUUID":"5c8576ac-172c-4d9a-a754-f97b7a078d3f","permissionDecision":{"decision":"accept","source":"config","reasonType":"rule","ruleSource":"cliArg"},"userType":"external","entrypoint":"sdk-cli","cwd":"/Users/simon-pierreboucher/wp29/runs/RC0094","sessionId":"989b99df-8772-4c22-b5b4-b743dc4be974","version":"2.1.314","gitBranch":"HEAD"}54{"type":"api-request-blob","sessionId":"989b99df-8772-4c22-b5b4-b743dc4be974","hash":"43ee518811e127c01829ca60aa38d0e3b7e7237fbd88925863fbdecdb2773744","message":{"role":"assistant","content":[{"type":"thinking","thinking":"","signature":"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"},{"type":"tool_use","id":"toolu_01Q53Q1ym3eAaHVyWrApqjNv","name":"Bash","input":{"command":"cat > out/analysis.py <<'EOF'\n\"\"\"F4-conf-02: verify six assertions against cited source extracts.\nReads only data/; writes out/results.json deterministically (no randomness).\"\"\"\nimport json, math, os, re\n\nROOT = os.path.dirname(os.path.dirname(os.path.abspath(__file__)))\nD = os.path.join(ROOT, \"data\")\nOUT = os.path.join(ROOT, \"out\")\n\ndef lines_of(p):\n with open(p, encoding=\"utf-8\") as f:\n return f.read().split(\"\\n\")\n\ndef wc_l(p):\n with open(p, \"rb\") as f:\n return f.read().count(b\"\\n\")\n\nassertions = json.load(open(os.path.join(D, \"assertions.json\"), encoding=\"utf-8\"))\nA = {a[\"id\"]: a for a in assertions}\nDCR, RES = \"arxiv-2609.27732v1\", \"arxiv-2606.14621v1\"\nsrc = {s: lines_of(os.path.join(D, \"sources\", s + \".txt\")) for s in (DCR, RES)}\n\ndef find(sid, pattern, start=0):\n \"\"\"Return (line_no, text) of first line at/after `start` matching regex.\"\"\"\n for i, l in enumerate(src[sid][start:], start=start):\n if re.search(pattern, l):\n return i + 1, l\n raise ValueError(f\"pattern {pattern!r} not found in {sid}\")\n\ndef show(tag, sid, ln, txt):\n print(f\"[{tag}] {sid}:{ln}: {txt.strip()}\")\n\ndef nums(s):\n return [float(x.replace(\",\", \"\")) for x in re.findall(r\"-?\\d[\\d,]*\\.?\\d*\", s)]\n\ndef cells(line):\n return [c.strip() for c in line.split(\"|\")]\n\ndef coef(c): # '-0.431**' -> -0.431\n return float(re.sub(r\"[*%]\", \"\", c))\n\ndef pct(b):\n return 100 * (math.exp(b) - 1)\n\ndef ci(b, se, z):\n return (b - z * se, b + z * se)\n\n# ---------- locate tables in DCR source ----------\nt6, _ = find(DCR, r\"^Table 6:\")\nln_att6, l_att6 = find(DCR, r\"^ATT \\|\", t6)\nln_se6, l_se6 = ln_att6 + 2, src[DCR][ln_att6 + 1]\nln_pc6, l_pc6 = find(DCR, r\"^% change \\|\", t6)\natt6 = [coef(c) for c in cells(l_att6)[1:]] # 1,3,5 km\nse6 = [float(c.strip(\"()\")) for c in cells(l_se6)[1:]]\npc6 = [coef(c) for c in cells(l_pc6)[1:]]\nstars6 = [c.count(\"*\") for c in cells(l_att6)[1:]]\n\nt7, _ = find(DCR, r\"^Table 7:\")\ndef t7row(name):\n ln, l = find(DCR, r\"^\" + re.escape(name) + r\" \\|\", t7)\n se_l = src[DCR][ln] # next-but-blank line holds SE (line ln+2 in 1-based)\n se_l = src[DCR][ln + 1]\n return ln, l, ln + 2, se_l, [coef(c) for c in cells(l)[1:]], [float(c.strip(\"()\")) for c in cells(se_l)[1:]]\nhiv = t7row(\"HIV\")\nhep = t7row(\"Hepatitis\")\n\nta19, _ = find(DCR, r\"^Table A19:\")\nln_a19, l_a19 = find(DCR, r\"^ATT \\|\", ta19)\nl_a19se = src[DCR][ln_a19 + 1]\nln_a19note, l_a19note = find(DCR, r\"never-treated comparison regions\", ta19)\n\nprint(\"=== Source lines relied on ===\")\nfor a in assertions:\n print(f\"{a['id']} (cites {a['cites']}): {a['text']}\")\nprint()\n\nverdicts, locators, reasons, details = {}, {}, {}, {}\n\n# ---------- A1 ----------\nshow(\"A1\", DCR, ln_att6, l_att6); show(\"A1\", DCR, ln_se6, l_se6); show(\"A1\", DCR, ln_pc6, l_pc6)\nb, se, st, p = att6[2], se6[2], stars6[2], pc6[2]\nok = (b == -0.431 and se == 0.210 and st == 2 and p == -35.0 and round(pct(b), 1) == -35.0\n and abs(b / se) > 1.96)\ndetails[\"A1\"] = {\"att\": b, \"se\": se, \"stars\": st, \"printed_pct\": p, \"computed_pct\": round(pct(b), 2),\n \"z\": round(b / se, 3)}\nverdicts[\"A1\"] = \"supported\" if ok else \"not_supported\"\nlocators[\"A1\"] = f'{DCR} | Table 6 | row \"ATT\" | column \"5 km\"'\nreasons[\"A1\"] = (\"Table 6 prints the 5 km ATT as -0.431** with SE (0.210) and % change -35.0% \"\n \"(100*(exp(-0.431)-1) = -35.0%), so estimate, SE, 5% significance and the 35.0% reduction all match.\")\n\n# ---------- A2 ----------\nshow(\"A2\", DCR, hiv[0], hiv[1]); show(\"A2\", DCR, hiv[2], hiv[3])\nb1 = hiv[4][0]\ndetails[\"A2\"] = {\"hiv_att_1km\": b1, \"hiv_se_1km\": hiv[5][0], \"asserted\": -0.063}\nverdicts[\"A2\"] = \"supported\" if b1 < 0 else \"not_supported\"\nlocators[\"A2\"] = f'{DCR} | Table 7 | row \"HIV\" | column \"1 km\"'\nreasons[\"A2\"] = (\"Table 7 prints the 1 km HIV ATT as +0.063 (SE 0.801), so the asserted negative sign \"\n \"(-0.063) and the claimed fall in HIV hospitalisations are contradicted.\")\n\n# ---------- A3 ----------\nshow(\"A3\", DCR, ln_att6, l_att6); show(\"A3\", DCR, ln_pc6, l_pc6)\nb3, p3 = att6[1], pc6[1]\ndetails[\"A3\"] = {\"att_3km\": b3, \"printed_pct_3km\": p3, \"computed_pct_3km\": round(pct(b3), 2), \"asserted_pct\": -28.3}\nverdicts[\"A3\"] = \"supported\" if abs(p3 - (-28.3)) < 0.05 else \"not_supported\"\nlocators[\"A3\"] = f'{DCR} | Table 6 | row \"% change\" | column \"3 km\"'\nreasons[\"A3\"] = (\"Table 6 converts the 3 km ATT of -0.283 to a -24.7% change (100*(exp(-0.283)-1) = -24.7%), \"\n \"so the asserted 28.3% reduction wrongly reads log points as percent.\")\n\n# ---------- A4 ----------\nshow(\"A4\", DCR, hep[0], hep[1]); show(\"A4\", DCR, hep[2], hep[3])\nb4, se4 = hep[4][2], hep[5][2]\nc196, c200, c1 = ci(b4, se4, 1.96), ci(b4, se4, 2.0), ci(b4, se4, 1.0)\nexcl196 = c196[0] > 0 or c196[1] < 0\nexcl200 = c200[0] > 0 or c200[1] < 0\ndetails[\"A4\"] = {\"att_5km\": b4, \"se_5km\": se4, \"ci95_z1.96\": [round(x, 3) for x in c196],\n \"ci95_z2.0\": [round(x, 3) for x in c200], \"pm_1se\": [round(x, 3) for x in c1],\n \"excludes_zero_z1.96\": excl196, \"excludes_zero_z2.0\": excl200,\n \"stars_printed\": hep[1].split(\"|\")[3].count(\"*\")}\nverdicts[\"A4\"] = \"supported\" if (excl196 and abs(c196[0] + 0.66) < 0.03 and abs(c196[1] + 0.16) < 0.03) else \"not_supported\"\nlocators[\"A4\"] = f'{DCR} | Table 7 | row \"Hepatitis\" | column \"5 km\"'\nreasons[\"A4\"] = (f\"Table 7 prints the 5 km hepatitis ATT as -0.406 (SE 0.250) with no star, giving a 95% CI of \"\n f\"[{c196[0]:.3f}, {c196[1]:.3f}] that includes zero; the asserted [-0.66, -0.16] is only +/-1 SE.\")\n\n# ---------- A5 ----------\nsex_hits = [(i + 1, l) for i, l in enumerate(src[DCR])\n if re.search(r\"\\b(men|women|male|female|sex|gender)\\b\", l, re.I)]\nprint(f\"[A5] lines in {DCR} mentioning men/women/male/female/sex/gender: {len(sex_hits)}\")\nfor ln, l in sex_hits:\n show(\"A5\", DCR, ln, l)\ndetails[\"A5\"] = {\"n_lines_mentioning_sex_or_gender\": len(sex_hits)}\nverdicts[\"A5\"] = \"not_assessable\" if not sex_hits else \"REVIEW\"\nlocators[\"A5\"] = f\"not reported in {DCR}\"\nreasons[\"A5\"] = (\"The extract reports ATTs only by buffer (Table 6) and diagnostic category (Table 7, Table A19) \"\n \"and contains no estimate by sex, so the men-versus-women comparison can be neither confirmed nor refuted.\")\n\n# ---------- A6 ----------\nln6, l6 = find(RES, r\"^Weeks on UI \\|\")\nshow(\"A6\", RES, ln6, l6)\nln6t, l6t = find(RES, r\"11\\.5% decrease\")\nshow(\"A6\", RES, ln6t, l6t[:0] + \"...a 1.99 week reduction in the number of weeks on UI (95% CI: [1.75 weeks, 2.24 weeks]; p<0.001) ... 11.5% decrease compared to the mean control group weeks on UI outcome of 17.3 weeks.\")\nc = cells(l6)\nate = c[4]; ctrl = c[2]\nate_n = nums(ate)\nctrl_mean = nums(ctrl)[0]\nest, lo, hi = ate_n[0], ate_n[-2], ate_n[-1]\nrel = 100 * est / ctrl_mean\ndetails[\"A6\"] = {\"ate\": est, \"ci95\": [lo, hi], \"control_mean\": ctrl_mean, \"computed_rel_pct\": round(rel, 2)}\nok6 = est == -1.99 and lo == -2.24 and hi == -1.75 and ctrl_mean == 17.3 and round(rel, 1) == -11.5\nverdicts[\"A6\"] = \"supported\" if ok6 else \"not_supported\"\nlocators[\"A6\"] = f'{RES} | Table 2 | row \"Weeks on UI\" | column \"Average treatment effect estimate\"'\nreasons[\"A6\"] = (\"Table 2 prints the ATE as -1.99 weeks with 95% CI [-2.24, -1.75] and a control mean of 17.3 weeks, \"\n \"and -1.99/17.3 = -11.5%, matching the text's 11.5% decrease.\")\n\n# ---------- naive baseline: do all numbers in the assertion appear verbatim in the cited source? ----------\nbaseline = {}\nfor a in assertions:\n text = src[a[\"cites\"]]\n blob = \"\\n\".join(text).replace(\"−\", \"-\")\n toks = re.findall(r\"\\d+(?:\\.\\d+)?\", a[\"text\"].replace(\"−\", \"-\"))\n toks = [t for t in toks if t not in (\"1\", \"3\", \"5\", \"95\")]\n baseline[a[\"id\"]] = all(t in blob for t in toks)\nprint(\"\\nNaive baseline (all numbers verbatim in source):\", baseline)\n\ndata_issues = [\n {\"issue\": f\"{DCR}: Table A19 prints the CS-DR 5 km ATT -0.431** with SE (0.218), whereas Table 6 prints the same estimate with SE (0.210).\",\n \"handling\": \"Table 6 (the main results table, the one A1 cites) is used as the locator for A1; A1's 5% significance also holds with SE 0.218 at z=1.96 (|t|=1.98), and the source prints ** in both tables.\"},\n {\"issue\": f\"{DCR}: Table A19 note says 640 never-treated comparison regions, while Table A19 body, Table 6 and the Figure 6 note say 608.\",\n \"handling\": \"Recorded only; no assertion depends on the control-region count.\"},\n {\"issue\": f\"{DCR}: abstract states fatal hospitalisations fall by 35%, but Table 7 5 km fatal ATT -0.354 implies -29.8% and Section 6.1 says approximately 30%.\",\n \"handling\": \"Recorded only; no assertion concerns fatal hospitalisations. Tables are treated as primary evidence.\"},\n {\"issue\": f\"{DCR}: Section 6 text calls HIV estimates 'close to zero' although Table 7 HIV ATTs at 3 km/5 km are -0.239/-0.340 (insignificant).\",\n \"handling\": \"A2 is decided by the Table 7 1 km cell (+0.063), not by the narrative.\"},\n {\"issue\": f\"{RES}: results text gives the weeks-on-UI CI as unsigned magnitudes [1.75 weeks, 2.24 weeks] while Table 2 prints the signed CI [-2.24, -1.75].\",\n \"handling\": \"Treated as the same interval expressed as a reduction; A6 is decided by Table 2.\"},\n {\"issue\": f\"{RES}: rendering defect 'p ¡ 0.001' in the short-term weeks-on-UI sentence.\",\n \"handling\": \"Read as p < 0.001 (consistent with Table 2); not decisive for any assertion.\"},\n]\n\nn_input_rows = {\"assertions.json\": len(assertions), \"README.md\": wc_l(os.path.join(D, \"README.md\"))}\nfor s in (DCR, RES):\n n_input_rows[s + \".txt\"] = wc_l(os.path.join(D, \"sources\", s + \".txt\"))\n\nvals = list(verdicts.values())\nresults = {\n \"task_id\": \"F4-conf-02\",\n \"verdicts\": verdicts,\n \"locators\": locators,\n \"reasons\": reasons,\n \"n_supported\": vals.count(\"supported\"),\n \"n_not_supported\": vals.count(\"not_supported\"),\n \"n_not_assessable\": vals.count(\"not_assessable\"),\n \"feasibility\": \"complete\",\n \"feasibility_reason\": None,\n \"data_issues\": data_issues,\n \"n_input_rows\": n_input_rows,\n \"n_analysed\": len(assertions),\n \"random_seed\": None,\n \"baseline_numeric_verbatim_match\": baseline,\n \"computation_details\": details,\n}\nos.makedirs(OUT, exist_ok=True)\nwith open(os.path.join(OUT, \"results.json\"), \"w\", encoding=\"utf-8\") as f:\n json.dump(results, f, indent=2, ensure_ascii=False)\nprint(\"\\nVerdicts:\", verdicts)\nprint(\"Counts: supported=%d not_supported=%d not_assessable=%d\" %\n (results[\"n_supported\"], results[\"n_not_supported\"], results[\"n_not_assessable\"]))\nEOF\n~/wp29/venv/bin/python out/analysis.py && cat out/results.json | head -80","description":"Write and run analysis 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se_a19, \"z_with_A19_se\": round(b / se_a19, 3)}''')\nopen(p,'w').write(s)\nEOF\n~/wp29/venv/bin/python out/analysis.py | grep -E \"A1\\]|A6\\]\"; cp out/results.json /tmp/r1.json; rm out/results.json; ~/wp29/venv/bin/python out/analysis.py >/dev/null; cmp out/results.json /tmp/r1.json && echo IDENTICAL; grep -A12 '\"A1\": {' out/results.json | tail -12","description":"Fix printing, rerun, check 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arxiv-2609.27732v1:36: ATT | -0.399 | -0.283 | -0.431**\n[A1] arxiv-2609.27732v1:38: | (0.412) | (0.279) | (0.210)\n[A1] arxiv-2609.27732v1:40: % change | -32.9% | -24.7% | -35.0%\n[A1] arxiv-2609.27732v1:121: ATT | -0.431** | -0.438** | -0.362* | -0.149***\n[A1] arxiv-2609.27732v1:123: | (0.218) | (0.208) | (0.205) | (0.038)\n[A6] arxiv-2606.14621v1:30: Weeks on UI | 15.2 weeks (SD: 9.3) | 17.3 weeks (SD: 9.4) | -2.10 weeks; p<0.001; 95% CI: [-2.34, -1.86] | -1.99 weeks; p<0.001; 95% CI: [-2.24, -1.75]\n[A6] arxiv-2606.14621v1:37: ...a 1.99 week reduction in the number of weeks on UI (95% CI: [1.75 weeks, 2.24 weeks]; p<0.001 ) due to RESEA selection. The latter is an 11.5% decrease compared to the mean control group weeks on UI outcome of 17.3 weeks.\nIDENTICAL\n \"att\": -0.431,\n \"se\": 0.21,\n \"stars\": 2,\n \"printed_pct\": -35.0,\n \"computed_pct\": -35.01,\n \"z\": -2.052,\n \"se_tableA19_CSDR\": 0.218,\n \"z_with_A19_se\": -1.977\n },\n \"A2\": {\n \"hiv_att_1km\": 0.063,\n \"hiv_se_1km\": 0.801,","is_error":false}]},"uuid":"343565ba-1140-4875-8ab6-fa045758177c","timestamp":"2026-10-30T05:30:42.334Z","toolUseResult":{"stdout":"[A1] arxiv-2609.27732v1:36: ATT | -0.399 | -0.283 | -0.431**\n[A1] arxiv-2609.27732v1:38: | (0.412) | (0.279) | (0.210)\n[A1] arxiv-2609.27732v1:40: % change | -32.9% | -24.7% | -35.0%\n[A1] arxiv-2609.27732v1:121: ATT | -0.431** | -0.438** | -0.362* | -0.149***\n[A1] arxiv-2609.27732v1:123: | (0.218) | (0.208) | (0.205) | (0.038)\n[A6] arxiv-2606.14621v1:30: Weeks on UI | 15.2 weeks (SD: 9.3) | 17.3 weeks (SD: 9.4) | -2.10 weeks; p<0.001; 95% CI: [-2.34, -1.86] | -1.99 weeks; p<0.001; 95% CI: [-2.24, -1.75]\n[A6] arxiv-2606.14621v1:37: ...a 1.99 week reduction in the number of weeks on UI (95% CI: [1.75 weeks, 2.24 weeks]; p<0.001 ) due to RESEA selection. The latter is an 11.5% decrease compared to the mean control group weeks on UI outcome of 17.3 weeks.\nIDENTICAL\n \"att\": -0.431,\n \"se\": 0.21,\n \"stars\": 2,\n \"printed_pct\": -35.0,\n \"computed_pct\": -35.01,\n \"z\": -2.052,\n \"se_tableA19_CSDR\": 0.218,\n \"z_with_A19_se\": -1.977\n },\n \"A2\": {\n \"hiv_att_1km\": 0.063,\n \"hiv_se_1km\": 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Handled: recorded as a source rounding data_issue (0.05 pp, likely unrounded coefficient); immaterial to the A3 verdict since asserted value is -28.3%. Reason text now states both values. 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identical within tolerance\nreceipt: /Users/simon-pierreboucher/wp29/runs/RC0094/out/state/gate_receipts/20261030T053105.234258Z.json\n20261030T053105.234258Z.json","is_error":false}]},"uuid":"643b477e-c915-4f4d-8eff-ee3c6b16cc99","timestamp":"2026-10-30T05:31:05.245Z","toolUseResult":{"stdout":"IDENTICAL\nPGAR GATE pgar_gate/1.0 — FAILED (10 of 27 checks failed)\n [ok] file:out/results.json: present\n [FAIL] file:out/report.md: missing or empty\n [ok] file:out/analysis.py: present\n [FAIL] file:out/claims.json: missing or empty\n [ok] results_json: parsed\n [ok] key:verdicts: ok\n [ok] key:locators: ok\n [ok] key:reasons: ok\n [ok] key:n_supported: ok\n [ok] key:n_not_supported: ok\n [ok] key:n_not_assessable: ok\n [ok] key:task_id: ok\n [ok] key:feasibility: ok\n [ok] key:feasibility_reason: ok\n [ok] key:data_issues: ok\n [ok] key:n_input_rows: ok\n [ok] key:n_analysed: ok\n [ok] key:random_seed: ok\n [FAIL] section:Question: heading not found\n [FAIL] section:Data and exclusions: heading not found\n [FAIL] section:Method: heading not found\n [FAIL] section:Results: heading not found\n [FAIL] section:Uncertainty: heading not found\n [FAIL] section:Limitations and open issues: heading not found\n [FAIL] claims_json: out/claims.json missing\n [FAIL] phase_ledger: phases not terminal: ['P2', 'P3', 'P4', 'P5']\n [ok] reproducibility: regenerated in 0.0s; 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A1–A5 cite Armendariz (2026), arXiv:2609.27732v1 (drug consumption rooms, Switzerland); A6 cites Li, Pearson-Merkowitz & Yokum (2026), arXiv:2606.14621v1 (Rhode Island RESEA trial).\n\n## Data and exclusions\nFour input files were read (`n_input_rows`): `assertions.json` (6 items), `README.md` (14 lines), `arxiv-2609.27732v1.txt` (134 lines), `arxiv-2606.14621v1.txt` (58 lines). Their SHA-256 hashes match the README and bundle (`out/state/data_audit.md`). No assertion was excluded (`out/exclusions.csv`: 6 in, 0 removed), so `n_analysed` = 6. The only evidence used was the extracts. I found seven issues inside the sources and recorded them in `data_issues`. They are: a Table 6 vs Table A19 standard-error mismatch for the same 5 km CS-DR estimate (0.210 vs 0.218); 608 vs 640 control regions; the abstract's \"35%\" fall in fatal hospitalisations vs −0.354 log points (≈ −29.8%); narrative text calling the HIV estimates \"close to zero\"; a 0.05 pp rounding gap in the 3 km \"% change\"; an unsigned confidence interval in the RESEA text; and a rendering defect (\"p ¡ 0.001\"). None of these decides a verdict.\n\n## Method\n`out/analysis.py` finds the relevant table rows by regex, reads the printed cells, prints the source lines it uses, and applies the task conventions. Percentage change is 100·(exp(b) − 1). A 95% CI is b ± 1.96·SE, with 2.0 as a sensitivity check. A relative change is ATE divided by the control mean. Each verdict rule is written explicitly in the script. A5 is checked by searching the cited extract for any sex or gender term (none were found). For a simpler comparison, a naive baseline asks only whether every number in an assertion appears verbatim in the source (`baseline_numeric_verbatim_match`). This baseline misses the sign error in A2 and the missing subgroup in A5, so it is not used for any verdict.\n\n## Results\n(`verdicts`; counts `n_supported` = 2, `n_not_supported` = 3, `n_not_assessable` = 1)\n\n| id | verdict | locator | decisive element |\n|---|---|---|---|\n| A1 | supported | Table 6, row \"ATT\", col \"5 km\" | Table 6 prints −0.431** with SE (0.210) and −35.0%. exp(−0.431) − 1 = −35.0% (`computation_details.A1`) |\n| A2 | not_supported | Table 7, row \"HIV\", col \"1 km\" | The printed ATT is **+0.063** (SE 0.801), so the sign is positive, not negative |\n| A3 | not_supported | Table 6, row \"% change\", col \"3 km\" | −0.283 log points is a −24.7% change (computed −24.6%), not −28.3%. The assertion treats log points as percent |\n| A4 | not_supported | Table 7, row \"Hepatitis\", col \"5 km\" | −0.406 ± 1.96·0.250 = [−0.896, 0.084], which includes zero (the estimate has no star). The asserted interval is ±1 SE |\n| A5 | not_assessable | not reported in arxiv-2609.27732v1 | The extract has no estimates by sex |\n| A6 | supported | RESEA Table 2, row \"Weeks on UI\", col \"ATE\" | Table 2 prints −1.99 weeks, CI [−2.24, −1.75], and a control mean of 17.3. −1.99/17.3 = −11.5% (`computation_details.A6`) |\n\nThe full one-sentence reasons are in `reasons`.\n\n## Uncertainty\nThe verdicts are categorical and involve no sampling randomness (`random_seed` = null). The places where a convention matters are listed below.\n- **A1, critical value:** z = −0.431/0.210 = −2.05 (`computation_details.A1.z`), which is significant at 5% with either 1.96 or 2.0, and the source prints `**`. If the Table A19 SE of 0.218 were used, z = −1.977 (`computation_details.A1.z_with_A19_se`). That is still significant at 1.96, but just short of 2.0. A1 itself quotes SE 0.210 from Table 6, and the source's own stars mark the estimate as significant at 5%, so the verdict stands. It would only become debatable if one replaced the source's SE with the appendix SE and used z = 2.0.\n- **A1 and A3, log-to-percent conversion:** exp(−0.431) − 1 = −35.01%, which matches the assertion. For A3, the 28.3% figure equals the log-point coefficient, while the exact conversion gives −24.6% to −24.7%. No reasonable conversion yields 28.3%, so A3 stays not_supported.\n- **A4, critical value:** the CI includes zero with 1.96 ([−0.896, 0.084]) and with 2.0 ([−0.906, 0.094]) (`computation_details.A4`). The asserted [−0.66, −0.16] matches only a ±1·SE band. The verdict is the same under either convention.\n- **A6:** the rounding of 11.50% does not affect the verdict. No convention is involved.\n- A2 and A5 do not depend on any convention.\n\n## Limitations and open issues\n- The verdicts rely only on the extracts. Omitted sections of the Swiss paper might contain sex-specific results, but by the task rules A5 must still be not_assessable, not refuted.\n- A1 rests on Table 6. The inconsistent SE in Table A19 for the same specification is an internal inconsistency in the source (`data_issues`), and I cannot resolve it from the extract.\n- The verdict rules in `analysis.py` encode my reading of the tables. They check the printed values programmatically, but the classification of each element (sign, magnitude, interval, significance, population) was my judgement.\n- The task is complete (`feasibility` = \"complete\").\nEOF\ncat > out/claims.json <<'EOF'\n[\n {\"id\":\"C1\",\"text\":\"A1 is supported: Table 6 prints the 5 km ATT -0.431** (SE 0.210), % change -35.0%.\",\"results_keys\":[\"verdicts\",\"locators\",\"reasons\",\"computation_details\"],\"status\":\"supported\",\"caveat\":\"Table A19 prints SE 0.218 for the same specification; significance at 5% then holds at z=1.96 but not at 2.0.\"},\n {\"id\":\"C2\",\"text\":\"A2 is not supported: the 1 km HIV ATT in Table 7 is +0.063, not negative.\",\"results_keys\":[\"verdicts\",\"locators\",\"reasons\"],\"status\":\"supported\",\"caveat\":\"\"},\n {\"id\":\"C3\",\"text\":\"A3 is not supported: -0.283 log points is a -24.7% change, not -28.3%.\",\"results_keys\":[\"verdicts\",\"locators\",\"reasons\",\"computation_details\"],\"status\":\"supported\",\"caveat\":\"Exact conversion gives -24.65% (rounds to -24.6%); printed -24.7%.\"},\n {\"id\":\"C4\",\"text\":\"A4 is not supported: the 95% CI for the 5 km hepatitis ATT is about [-0.896, 0.084] and includes zero.\",\"results_keys\":[\"verdicts\",\"locators\",\"reasons\",\"computation_details\"],\"status\":\"supported\",\"caveat\":\"Same conclusion with critical value 2.0.\"},\n {\"id\":\"C5\",\"text\":\"A5 is not assessable: the extract reports no estimates by sex.\",\"results_keys\":[\"verdicts\",\"locators\",\"reasons\"],\"status\":\"supported\",\"caveat\":\"Omitted sections of the paper may contain such results; they are inadmissible here.\"},\n {\"id\":\"C6\",\"text\":\"A6 is supported: Table 2 prints ATE -1.99 weeks, 95% CI [-2.24, -1.75], control mean 17.3; -1.99/17.3 = -11.5%.\",\"results_keys\":[\"verdicts\",\"locators\",\"reasons\",\"computation_details\"],\"status\":\"supported\",\"caveat\":\"\"},\n {\"id\":\"C7\",\"text\":\"Counts: 2 supported, 3 not supported, 1 not assessable over 6 analysed assertions; task complete.\",\"results_keys\":[\"n_supported\",\"n_not_supported\",\"n_not_assessable\",\"n_analysed\",\"feasibility\"],\"status\":\"supported\",\"caveat\":\"\"},\n {\"id\":\"C8\",\"text\":\"The sources contain seven internal inconsistencies or rendering defects, none decisive for any verdict.\",\"results_keys\":[\"data_issues\"],\"status\":\"supported\",\"caveat\":\"\"}\n]\nEOF\n~/wp29/venv/bin/python - <<'EOF'\nimport json;p=json.load(open('out/state/phases.json'))\np['P5']={\"status\":\"passed\",\"checks\":[\"report.md written with 6 required sections, quantitative statements cite results keys\",\"claims.json written (8 claims, all keys exist)\",\"gate run 2 at end of P5 (see receipt below)\"],\"notes\":\"\"}\njson.dump(p,open('out/state/phases.json','w'),indent=1)\nEOF\n~/wp29/venv/bin/python ~/wp29/gates/pgar_gate.py . | tail -5; 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identical within tolerance\nreceipt: /Users/simon-pierreboucher/wp29/runs/RC0094/out/state/gate_receipts/20261030T053141.480048Z.json\n20261030T053105.234258Z.json\n20261030T053141.480048Z.json","is_error":false}]},"uuid":"fa9aa2b0-1d97-4382-9cb1-7c9f984c8535","timestamp":"2026-10-30T05:31:41.492Z","toolUseResult":{"stdout":" [ok] section:Limitations and open issues: present\n [ok] claims_json: 8 claims, all keys resolve\n [ok] phase_ledger: consistent\n [ok] reproducibility: regenerated in 0.0s; identical within tolerance\nreceipt: /Users/simon-pierreboucher/wp29/runs/RC0094/out/state/gate_receipts/20261030T053141.480048Z.json\n20261030T053105.234258Z.json\n20261030T053141.480048Z.json","stderr":"","interrupted":false,"isImage":false,"noOutputExpected":false},"sandboxed":false,"sourceToolAssistantUUID":"955205af-7628-4f7f-a812-e10722a3b8f2","permissionDecision":{"decision":"accept","source":"config","reasonType":"rule","ruleSource":"cliArg"},"userType":"external","entrypoint":"sdk-cli","cwd":"/Users/simon-pierreboucher/wp29/runs/RC0094","sessionId":"989b99df-8772-4c22-b5b4-b743dc4be974","version":"2.1.314","gitBranch":"HEAD"}89{"type":"api-request-blob","sessionId":"989b99df-8772-4c22-b5b4-b743dc4be974","hash":"6425a5b7df7df1cea1d73c21d66218016f885ab0b134b609269faf832abe6bd9","message":{"role":"assistant","content":[{"type":"tool_use","id":"toolu_01XGiUaz1GKsaJhgSrfYfoTD","name":"Bash","input":{"command":"cat > out/report.md <<'EOF'\n# F4-conf-02 — Are the six assertions supported by their cited sources?\n\n## Question\nFor each of six assertions in `data/assertions.json`, decide from the cited extract alone whether it is supported, not_supported or not_assessable, giving one locator and a one-sentence reason (keys `verdicts`, `locators`, `reasons`). A1–A5 cite Armendariz (2026), arXiv:2609.27732v1 (drug consumption rooms, Switzerland); A6 cites Li, Pearson-Merkowitz & Yokum (2026), arXiv:2606.14621v1 (Rhode Island RESEA trial).\n\n## Data and exclusions\nFour input files were read (`n_input_rows`): `assertions.json` (6 items), `README.md` (14 lines), `arxiv-2609.27732v1.txt` (134 lines), `arxiv-2606.14621v1.txt` (58 lines). Their SHA-256 hashes match the README and bundle (`out/state/data_audit.md`). No assertion was excluded (`out/exclusions.csv`: 6 in, 0 removed), so `n_analysed` = 6. The only evidence used was the extracts. I found seven issues inside the sources and recorded them in `data_issues`. They are: a Table 6 vs Table A19 standard-error mismatch for the same 5 km CS-DR estimate (0.210 vs 0.218); 608 vs 640 control regions; the abstract's \"35%\" fall in fatal hospitalisations vs −0.354 log points (≈ −29.8%); narrative text calling the HIV estimates \"close to zero\"; a 0.05 pp rounding gap in the 3 km \"% change\"; an unsigned confidence interval in the RESEA text; and a rendering defect (\"p ¡ 0.001\"). None of these decides a verdict.\n\n## Method\n`out/analysis.py` finds the relevant table rows by regex, reads the printed cells, prints the source lines it uses, and applies the task conventions. Percentage change is 100·(exp(b) − 1). A 95% CI is b ± 1.96·SE, with 2.0 as a sensitivity check. A relative change is ATE divided by the control mean. Each verdict rule is written explicitly in the script. A5 is checked by searching the cited extract for any sex or gender term (none were found). For a simpler comparison, a naive baseline asks only whether every number in an assertion appears verbatim in the source (`baseline_numeric_verbatim_match`). This baseline misses the sign error in A2 and the missing subgroup in A5, so it is not used for any verdict.\n\n## Results\n(`verdicts`; counts `n_supported` = 2, `n_not_supported` = 3, `n_not_assessable` = 1)\n\n| id | verdict | locator | decisive element |\n|---|---|---|---|\n| A1 | supported | Table 6, row \"ATT\", col \"5 km\" | Table 6 prints −0.431** with SE (0.210) and −35.0%. exp(−0.431) − 1 = −35.0% (`computation_details.A1`) |\n| A2 | not_supported | Table 7, row \"HIV\", col \"1 km\" | The printed ATT is **+0.063** (SE 0.801), so the sign is positive, not negative |\n| A3 | not_supported | Table 6, row \"% change\", col \"3 km\" | −0.283 log points is a −24.7% change (computed −24.6%), not −28.3%. The assertion treats log points as percent |\n| A4 | not_supported | Table 7, row \"Hepatitis\", col \"5 km\" | −0.406 ± 1.96·0.250 = [−0.896, 0.084], which includes zero (the estimate has no star). The asserted interval is ±1 SE |\n| A5 | not_assessable | not reported in arxiv-2609.27732v1 | The extract has no estimates by sex |\n| A6 | supported | RESEA Table 2, row \"Weeks on UI\", col \"ATE\" | Table 2 prints −1.99 weeks, CI [−2.24, −1.75], and a control mean of 17.3. −1.99/17.3 = −11.5% (`computation_details.A6`) |\n\nThe full one-sentence reasons are in `reasons`.\n\n## Uncertainty\nThe verdicts are categorical and involve no sampling randomness (`random_seed` = null). The places where a convention matters are listed below.\n- **A1, critical value:** z = −0.431/0.210 = −2.05 (`computation_details.A1.z`), which is significant at 5% with either 1.96 or 2.0, and the source prints `**`. If the Table A19 SE of 0.218 were used, z = −1.977 (`computation_details.A1.z_with_A19_se`). That is still significant at 1.96, but just short of 2.0. A1 itself quotes SE 0.210 from Table 6, and the source's own stars mark the estimate as significant at 5%, so the verdict stands. It would only become debatable if one replaced the source's SE with the appendix SE and used z = 2.0.\n- **A1 and A3, log-to-percent conversion:** exp(−0.431) − 1 = −35.01%, which matches the assertion. For A3, the 28.3% figure equals the log-point coefficient, while the exact conversion gives −24.6% to −24.7%. No reasonable conversion yields 28.3%, so A3 stays not_supported.\n- **A4, critical value:** the CI includes zero with 1.96 ([−0.896, 0.084]) and with 2.0 ([−0.906, 0.094]) (`computation_details.A4`). The asserted [−0.66, −0.16] matches only a ±1·SE band. The verdict is the same under either convention.\n- **A6:** the rounding of 11.50% does not affect the verdict. No convention is involved.\n- A2 and A5 do not depend on any convention.\n\n## Limitations and open issues\n- The verdicts rely only on the extracts. Omitted sections of the Swiss paper might contain sex-specific results, but by the task rules A5 must still be not_assessable, not refuted.\n- A1 rests on Table 6. The inconsistent SE in Table A19 for the same specification is an internal inconsistency in the source (`data_issues`), and I cannot resolve it from the extract.\n- The verdict rules in `analysis.py` encode my reading of the tables. They check the printed values programmatically, but the classification of each element (sign, magnitude, interval, significance, population) was my judgement.\n- The task is complete (`feasibility` = \"complete\").\nEOF\ncat > out/claims.json <<'EOF'\n[\n {\"id\":\"C1\",\"text\":\"A1 is supported: Table 6 prints the 5 km ATT -0.431** (SE 0.210), % change -35.0%.\",\"results_keys\":[\"verdicts\",\"locators\",\"reasons\",\"computation_details\"],\"status\":\"supported\",\"caveat\":\"Table A19 prints SE 0.218 for the same specification; significance at 5% then holds at z=1.96 but not at 2.0.\"},\n {\"id\":\"C2\",\"text\":\"A2 is not supported: the 1 km HIV ATT in Table 7 is +0.063, not negative.\",\"results_keys\":[\"verdicts\",\"locators\",\"reasons\"],\"status\":\"supported\",\"caveat\":\"\"},\n {\"id\":\"C3\",\"text\":\"A3 is not supported: -0.283 log points is a -24.7% change, not -28.3%.\",\"results_keys\":[\"verdicts\",\"locators\",\"reasons\",\"computation_details\"],\"status\":\"supported\",\"caveat\":\"Exact conversion gives -24.65% (rounds to -24.6%); printed -24.7%.\"},\n {\"id\":\"C4\",\"text\":\"A4 is not supported: the 95% CI for the 5 km hepatitis ATT is about [-0.896, 0.084] and includes zero.\",\"results_keys\":[\"verdicts\",\"locators\",\"reasons\",\"computation_details\"],\"status\":\"supported\",\"caveat\":\"Same conclusion with critical value 2.0.\"},\n {\"id\":\"C5\",\"text\":\"A5 is not assessable: the extract reports no estimates by sex.\",\"results_keys\":[\"verdicts\",\"locators\",\"reasons\"],\"status\":\"supported\",\"caveat\":\"Omitted sections of the paper may contain such results; they are inadmissible here.\"},\n {\"id\":\"C6\",\"text\":\"A6 is supported: Table 2 prints ATE -1.99 weeks, 95% CI [-2.24, -1.75], control mean 17.3; -1.99/17.3 = -11.5%.\",\"results_keys\":[\"verdicts\",\"locators\",\"reasons\",\"computation_details\"],\"status\":\"supported\",\"caveat\":\"\"},\n {\"id\":\"C7\",\"text\":\"Counts: 2 supported, 3 not supported, 1 not assessable over 6 analysed assertions; task complete.\",\"results_keys\":[\"n_supported\",\"n_not_supported\",\"n_not_assessable\",\"n_analysed\",\"feasibility\"],\"status\":\"supported\",\"caveat\":\"\"},\n {\"id\":\"C8\",\"text\":\"The sources contain seven internal inconsistencies or rendering defects, none decisive for any verdict.\",\"results_keys\":[\"data_issues\"],\"status\":\"supported\",\"caveat\":\"\"}\n]\nEOF\n~/wp29/venv/bin/python - <<'EOF'\nimport json;p=json.load(open('out/state/phases.json'))\np['P5']={\"status\":\"passed\",\"checks\":[\"report.md written with 6 required sections, quantitative statements cite results keys\",\"claims.json written (8 claims, all keys exist)\",\"gate run 2 at end of P5 (see receipt below)\"],\"notes\":\"\"}\njson.dump(p,open('out/state/phases.json','w'),indent=1)\nEOF\n~/wp29/venv/bin/python ~/wp29/gates/pgar_gate.py . | tail -5; 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The script `out/analysis.py` regenerates the results identically from `data/`, and the final gate run passes all 27 checks.\n\n| id | verdict | what decides it |\n|---|---|---|\n| A1 | supported | Table 6, 5 km: −0.431** with SE (0.210) and −35.0%; exp(−0.431) − 1 = −35.0% |\n| A2 | not supported | Table 7 prints the 1 km HIV estimate as **+0.063**, not −0.063, so it does not show a fall |\n| A3 | not supported | −0.283 log points is a −24.7% change (Table 6); the 28.3% treats log points as a percentage |\n| A4 | not supported | Hepatitis at 5 km: −0.406 ± 1.96·0.250 gives [−0.896, 0.084], which includes zero; the claimed [−0.66, −0.16] is only ±1 standard error |\n| A5 | not assessable | The extract reports nothing by sex, so the men-versus-women comparison can't be judged |\n| A6 | supported | RESEA Table 2: −1.99 weeks, 95% CI [−2.24, −1.75], control mean 17.3; −1.99/17.3 = −11.5% |\n\nChanging the critical value from 1.96 to 2.0 doesn't change any verdict.\n\nThe sources contain seven internal inconsistencies, none of which decides a verdict:\n- **Standard error mismatch (Swiss paper):** the same 5 km estimate has a standard error of 0.218 in appendix Table A19 but 0.210 in Table 6. With 0.218, A1's 5% significance holds at 1.96 (z = −1.98) but just misses at 2.0. I kept A1 as supported because it quotes Table 6, and the source marks the estimate as significant in both tables.\n- **Control-region count:** 608 in the tables, 640 in the Table A19 note.\n- **Fatal hospitalisations:** the abstract says they fall 35%, but the table estimate of −0.354 implies about −29.8% (the text itself says about 30%).\n- **HIV wording:** the text calls the HIV estimates \"close to zero\", though at 3 km and 5 km they are −0.239 and −0.340 (not significant).\n- **3 km rounding:** exp(−0.283) − 1 = −24.65%, which rounds to −24.6%, against the printed −24.7%. This tripped one of my own consistency checks; it is a source rounding issue and doesn't affect A3.\n- **RESEA text:** the confidence interval is written without signs, and one line has a rendering defect (\"p ¡ 0.001\").\n\n**Limitation:** the omitted sections of the Swiss paper might contain results by sex, but the task rules mean A5 stays not assessable.\n\nEverything is in `out/`; start with `report.md`, with the verdicts in `results.json`."}],"container":null,"stop_reason":"end_turn","stop_sequence":null,"stop_details":null,"usage":{"input_tokens":2,"cache_creation_input_tokens":417,"cache_read_input_tokens":44123,"output_tokens":994,"output_tokens_details":{"thinking_tokens":0},"server_tool_use":{"web_search_requests":0,"web_fetch_requests":0},"service_tier":"standard","cache_creation":{"ephemeral_1h_input_tokens":0,"ephemeral_5m_input_tokens":417},"inference_geo":"global","iterations":[],"speed":"standard","fallback_credit":null},"input_transformations":[],"diagnostics":null,"context_management":null},"apiBlockIndex":0,"requestId":"req_011CgXsdz3mHt8PXb4mA3iA5","requestRef":"0e5bb8bf-5ce9-42b3-9737-1623c26851f8","requestedModel":"claude-opus-5-5","type":"assistant","uuid":"8854cff9-820c-42f6-85ae-9521eb0ae1b7","timestamp":"2026-10-30T05:31:54.904Z","effort":"medium","perTurnEffort":"medium","userType":"external","entrypoint":"sdk-cli","cwd":"/Users/simon-pierreboucher/wp29/runs/RC0094","sessionId":"989b99df-8772-4c22-b5b4-b743dc4be974","version":"2.1.314","gitBranch":"HEAD"}97{"type":"last-prompt","lastPrompt":"Begin","leafUuid":"8854cff9-820c-42f6-85ae-9521eb0ae1b7","sessionId":"989b99df-8772-4c22-b5b4-b743dc4be974"}98{"type":"cost-state","sessionId":"989b99df-8772-4c22-b5b4-b743dc4be974","totalCostUSD":0.6852390000000002,"totalAPIDuration":173297,"totalAPIDurationWithoutRetries":173288,"totalToolDuration":1003,"totalLinesAdded":0,"totalLinesRemoved":0,"totalDuration":174453,"startTime":1793338140459,"modelUsage":{"claude-opus-5-5":{"inputTokens":32,"outputTokens":19476,"thinkingTokens":2096,"cacheReadInputTokens":402055,"cacheCreationInputTokens":43036,"cacheCreationEphemeral5mInputTokens":43036,"cacheCreationEphemeral1hInputTokens":0,"webSearchRequests":0,"costUSD":0.6852390000000002}},"hasUnknownModelCost":false}99