Scholarly upgrade v1.2: +32 verified references, new Discussion section
Phase 1: critical assessment (PAPER_REVIEW.md). Phase 2: 32 new references across 11 identified gaps (urban spatial structure, land share, supply constraints, price indices, submarkets, spatial-dependence empirics, capitalization theory, list-price microstructure, AVM/mass appraisal, Canadian evidence, HDFE methodology) — every entry verified against Crossref DOI records or publisher sources; references.bib 32 → 64. Phase 3: introduction deepened with numbered contributions; related work restructured into 7 thematic subsections each ending with an explicit gap statement; methodology choices grounded in citations; new Discussion section (magnitudes vs. literature, points of tension, implications, limitations, future work); conclusion strengthened. Paper 26 → 34 pages. Phase 4: UPGRADE_REPORT.md with per-reference justifications and flagged claims. No result, number, figure or table changed. Co-Authored-By: Claude Fable 5 <noreply@anthropic.com>
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PAPER_REVIEW.md
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| 1 | +# PAPER_REVIEW — Critical assessment before the scholarly upgrade (2026-08-05) | |
| 2 | + | |
| 3 | +Scope: `paper/` (v1.1, 26 pp., 32 references). Assessment only — no results questioned. | |
| 4 | + | |
| 5 | +## 1. Core contribution: is it clearly stated? | |
| 6 | + | |
| 7 | +The empirical contribution is clear and genuinely stated in one sentence: *a national-scale | |
| 8 | +decomposition of Canadian house prices into structure vs. location using 1,153 absorbed FSA | |
| 9 | +fixed effects on 140,931 listings*. Three supporting claims (elasticity ≈ 0.55, bathrooms | |
| 10 | +≈ +11%, bedrooms ≈ 0; OOS R² 0.764; premia span ×9) are quantified and reproducible. | |
| 11 | + | |
| 12 | +**Weaknesses in the contribution statement:** | |
| 13 | +- The introduction motivates in three bullets ("first-order question", "granular data", | |
| 14 | + "transparent benchmark") but never states *what is new relative to specific prior work*. | |
| 15 | + No named paper is identified as the closest antecedent, so the gap is asserted, not shown. | |
| 16 | +- "Among the most geographically comprehensive single-equation hedonic exercises for | |
| 17 | + Canada" is unverifiable as written because the Canadian empirical hedonic record | |
| 18 | + (Des Rosiers/Thériault's Quebec program, Toronto and Vancouver studies) is never cited. | |
| 19 | +- The headline result — location ≈ 30 pp of R² — is never connected to the macro | |
| 20 | + literature quantifying the land/location share of housing value (Davis–Heathcote; | |
| 21 | + Knoll–Schularick–Steger), which is the natural external benchmark for its magnitude. | |
| 22 | + | |
| 23 | +## 2. Literature review: gaps by subfield | |
| 24 | + | |
| 25 | +Current coverage (good): Rosen framework and second-stage identification; semi-log | |
| 26 | +functional form; spatial econometrics vs. fixed effects debate; three amenity | |
| 27 | +capitalization classics; brief AVM motivation. | |
| 28 | + | |
| 29 | +**Missing subfields (each currently has zero citations):** | |
| 30 | + | |
| 31 | +1. **Urban spatial structure / monocentric city.** The paper estimates an urban price | |
| 32 | + gradient (§ Results 5.6) with no reference to Alonso–Muth–Mills, nor to modern | |
| 33 | + quantitative treatments (Ahlfeldt–Redding–Sturm–Wolf; Duranton–Puga). The gradient | |
| 34 | + section cites only Combes et al. (2015). | |
| 35 | +2. **Land value and the location share.** Davis & Heathcote (2007), Knoll, Schularick & | |
| 36 | + Steger (2017), Albouy's work on urban land values. Directly benchmark the 30-pp claim. | |
| 37 | +3. **House-price indices.** The hedonic/repeat-sales index literature (Bailey–Muth–Nourse; | |
| 38 | + Case–Shiller; Hill's survey) — the paper claims relevance for "house-price indices" in | |
| 39 | + the first paragraph without citing any index paper. | |
| 40 | +4. **Housing submarkets.** Goodman & Thibodeau; Bourassa et al. on submarket definitions — | |
| 41 | + the FSA-fixed-effect design is a submarket argument and should engage this strand. | |
| 42 | +5. **Spatial dependence in hedonics (empirics).** Dubin (1988); Basu & Thibodeau (1998); | |
| 43 | + and the Canadian spatio-temporal work of Dubé & Legros. Moran's I is used but only | |
| 44 | + Moran (1950) is cited. | |
| 45 | +6. **Capitalization theory.** Tiebout (1956), Oates (1969), Roback (1982) — the FSA | |
| 46 | + premium is interpreted as capitalized amenities with no reference to why amenities | |
| 47 | + capitalize. | |
| 48 | +7. **List price vs. transaction price.** The central data caveat (list prices) has no | |
| 49 | + citation — Genesove & Mayer (2001) on seller behaviour, Han & Strange (2015) on the | |
| 50 | + listing/search microstructure. | |
| 51 | +8. **AVM / ML valuation empirics.** One citation (Mullainathan & Spiess 2017). Missing the | |
| 52 | + applied mass-appraisal accuracy literature and the ML-vs-hedonic horse-race studies the | |
| 53 | + OOS section implicitly competes with. | |
| 54 | +9. **Canadian housing.** One CMHC report. Missing the Canadian hedonic tradition | |
| 55 | + (Des Rosiers and coauthors on Quebec; Toronto/Vancouver-specific studies) and the | |
| 56 | + supply-side explanations for Vancouver/Toronto price levels (Saiz-style constraints; | |
| 57 | + superstar-city dynamics of Gyourko–Mayer–Sinai). | |
| 58 | +10. **High-dimensional FE methodology.** Correia (2017) is cited, but the intellectual | |
| 59 | + origin (Abowd–Kramarz–Margolis) and the standard computational references | |
| 60 | + (Guimarães & Portugal) are not. | |
| 61 | +11. **Sample selection / trimming practice.** The 1% trim and its robustness variants have | |
| 62 | + no methodological anchor. | |
| 63 | + | |
| 64 | +## 3. Weak argumentation / unsupported claims | |
| 65 | + | |
| 66 | +- "Competitive with commercial automated valuation models" (§ Robustness, Conclusion) — | |
| 67 | + no AVM accuracy benchmark is cited; needs at least one accuracy-standard reference | |
| 68 | + (e.g., IAAO mass-appraisal standards or a published Zestimate-type accuracy figure). | |
| 69 | +- "Credible national estimates for Canada are scarce" — unsupported; requires citing what | |
| 70 | + *does* exist to establish scarcity. | |
| 71 | +- Half-bath negative coefficient interpretation ("older or more compartmentalised floor | |
| 72 | + plans") is speculative and unflagged — should be presented as conjecture or supported. | |
| 73 | +- "This is the housing counterpart of the within estimator" — fine, but the AKM/FE lineage | |
| 74 | + should be cited where the claim is made. | |
| 75 | +- The bedrooms≈0 result is called "a textbook hedonic finding" without a supporting | |
| 76 | + citation (Sirmans et al. tabulate mixed signs — an easy, honest anchor). | |
| 77 | +- Urban gradient "classic urban theory predicts" — no Alonso/Muth/Mills citation. | |
| 78 | + | |
| 79 | +## 4. Underdeveloped sections | |
| 80 | + | |
| 81 | +- **Introduction** (~1 page): thin on stakes (housing = largest household asset class; | |
| 82 | + assessment/taxation machinery; index construction) and has no explicit numbered | |
| 83 | + contribution list. | |
| 84 | +- **Related work** (~1.5 pages): organized adequately by theme but shallow within themes | |
| 85 | + (2–4 citations each) and never says *where the gap is* at the end of each strand. | |
| 86 | +- **Discussion: absent.** Results flow directly into robustness and a short conclusion. | |
| 87 | + There is no section interpreting magnitudes against prior literature (is 0.55 a typical | |
| 88 | + elasticity? is an 11% bathroom premium high? is ×9 premia dispersion large vs. the US?), | |
| 89 | + no engagement with findings that could contradict (e.g., submarket papers arguing | |
| 90 | + *coefficients*, not just intercepts, vary by location — which the paper's own | |
| 91 | + heterogeneity section partially confirms), and no consolidated Limitations & Future Work | |
| 92 | + (currently squeezed into two conclusion paragraphs). | |
| 93 | +- **Methodology**: several choices uncited (trimming, FSA pooling threshold, kNN Moran | |
| 94 | + implementation choice, quantile regression estimator details). | |
| 95 | + | |
| 96 | +## 5. Positioning: current vs. ideal | |
| 97 | + | |
| 98 | +**Current:** a well-executed measurement paper that reads as a technical report — it | |
| 99 | +presents itself mainly as "we ran a big transparent regression." | |
| 100 | + | |
| 101 | +**Ideal:** a contribution at the intersection of (i) the classic structure-vs-location | |
| 102 | +decomposition, (ii) the land-share macro literature, and (iii) the AVM benchmarking | |
| 103 | +debate — i.e., "the neighbourhood is the single largest priced component of Canadian | |
| 104 | +housing; we quantify it with a design that is transparent enough to audit and accurate | |
| 105 | +enough to rival black-box AVMs." The framing should name its closest antecedents (US | |
| 106 | +land-share estimates; submarket hedonics; ML-valuation horse races) and state exactly | |
| 107 | +what is new: national scope for Canada, listing-level granularity, absorbed-FE scale, and | |
| 108 | +a validated accuracy claim. | |
| 109 | + | |
| 110 | +## 6. Consequences for the upgrade (implemented in Phases 2–3) | |
| 111 | + | |
| 112 | +1. Add ~28 verified references across the 11 gaps above (target ≈ 60 total). | |
| 113 | +2. Restructure Related Work into thematic subsections, each ending with the gap. | |
| 114 | +3. Add a proper **Discussion** section: magnitudes vs. literature, agreements/ | |
| 115 | + disagreements, implications (assessment, taxation, indices, AVM), limitations & future | |
| 116 | + work. | |
| 117 | +4. Deepen the introduction (stakes, numbered contributions, roadmap); strengthen the | |
| 118 | + conclusion without overselling. | |
| 119 | +5. Ground every methodological choice in a citation; keep every number, figure and table | |
| 120 | + untouched. | |
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UPGRADE_REPORT.md
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| 1 | +# UPGRADE_REPORT — Scholarly upgrade of WP9 (v1.1 → v1.2, 2026-08-05) | |
| 2 | + | |
| 3 | +Scope: literature and framing only. **No result, number, figure or table changed.** | |
| 4 | +Paper: 26 → **34 pages** (+31%); references: 32 → **64** (63 cited); new **Discussion** | |
| 5 | +section (§7). Critical pre-assessment in `PAPER_REVIEW.md`. Builds cleanly | |
| 6 | +(pdflatex + bibtex, zero errors/undefined citations). | |
| 7 | + | |
| 8 | +## 1. New references (32), each verified before entry | |
| 9 | + | |
| 10 | +Verification method: direct Crossref DOI lookup for 30 entries (metadata in the .bib | |
| 11 | +copied from the Crossref record); Mills (1967) and the two books confirmed via JSTOR | |
| 12 | +issue listing / publisher records ([Mills 1967 AER 57(2):197–210](https://www.jstor.org/stable/i331577), | |
| 13 | +[Alonso 1964](https://www.cambridge.org/core/journals/journal-of-the-history-of-economic-thought/article/abs/william-alonso-richard-muth-resources-for-the-future-and-the-founding-of-urban-economics/A1F19C2F841A0D0AA33D15F46918CFEA), | |
| 14 | +[Muth 1969](https://www.cambridge.org/core/journals/recherches-economiques-de-louvain-louvain-economic-review/article/abs/rf-muth-cities-and-housing-the-spatial-pattern-of-urban-residential-land-use-chicago-and-london-the-university-of-chicago-press-1969-xxii-p-355-p-90/0AA8AA64AD2123A62CED306A63423327), | |
| 15 | +[Case–Shiller 1989 AER 79(1):125–137](https://econpapers.repec.org/RePEc:aea:aecrev:v:79:y:1989:i:1:p:125-37)). | |
| 16 | +The OpenAlex MCP connector was budget-limited, so Crossref's REST API was used instead. | |
| 17 | + | |
| 18 | +**Urban spatial structure (motivates the gradient section, previously uncited):** | |
| 19 | +- `alonso1964location` — founding monocentric land-rent model. | |
| 20 | +- `muth1969cities` — housing version of the monocentric model. | |
| 21 | +- `mills1967aggregative` — the third leg of the Alonso–Muth–Mills tradition. | |
| 22 | +- `ahlfeldt2015density` — modern quantitative estimation of density/amenity gradients (Berlin Wall). | |
| 23 | + | |
| 24 | +**Land value & the location share (external benchmark for the 30-pp headline):** | |
| 25 | +- `davis2007price` — U.S. residential land share ≈ 46%; direct macro counterpart. | |
| 26 | +- `knoll2017no` — land explains ~80% of global house-price growth since 1950. | |
| 27 | +- `albouy2016cities` — cross-city dispersion of land rents & amenity values. | |
| 28 | +- `cheshire1995price` — early land-price/amenity decomposition. | |
| 29 | + | |
| 30 | +**Supply constraints / superstar cities (explains WHY premia disperse ×9):** | |
| 31 | +- `saiz2010geographic` — geographic supply constraints; Vancouver-type geography. | |
| 32 | +- `gyourko2013superstar` — superstar-city price dynamics; frames Vancouver/Toronto. | |
| 33 | + | |
| 34 | +**House-price indices (paper claimed index relevance with zero index citations):** | |
| 35 | +- `bailey1963regression` — repeat-sales method origin. | |
| 36 | +- `case1989efficiency` — the index tradition + efficiency questions (also cited in Limitations). | |
| 37 | +- `hill2013hedonic` — authoritative survey of hedonic price indexes. | |
| 38 | + | |
| 39 | +**Submarkets (the FSA design is a submarket argument):** | |
| 40 | +- `goodman1998housing` — market segmentation tests. | |
| 41 | +- `bourassa2003submarkets` — submarkets improve prediction; simple geography suffices. | |
| 42 | + | |
| 43 | +**Spatial dependence, empirics (Moran's I had one 1950 citation):** | |
| 44 | +- `dubin1988estimation` — spatially autocorrelated errors distort hedonic inference. | |
| 45 | +- `basu1998analysis` — canonical measurement of residual spatial autocorrelation. | |
| 46 | +- `dube2013spatiotemporal` — Canadian spatio-temporal weights (Dubé & Legros). | |
| 47 | + | |
| 48 | +**Capitalization theory (why a neighbourhood intercept is 'value' at all):** | |
| 49 | +- `tiebout1956pure` — sorting on local public goods. | |
| 50 | +- `oates1969effects` — first capitalization measurement. | |
| 51 | +- `roback1982wages` — spatial-equilibrium amenity capitalization. | |
| 52 | + | |
| 53 | +**Hedonic identification:** | |
| 54 | +- `epple1987hedonic` — second-stage simultaneity; grounds our first-stage-only stance. | |
| 55 | + | |
| 56 | +**List prices & microstructure (the paper's central data caveat, previously uncited):** | |
| 57 | +- `genesove2001loss` — sellers set list prices strategically (loss aversion). | |
| 58 | +- `han2015microstructure` — search/bargaining microstructure (Handbook chapter). | |
| 59 | +- `kiel2008location` — the '3L' structure/location decomposition framework. | |
| 60 | + | |
| 61 | +**AVM / mass appraisal (grounds 'competitive with commercial AVMs'):** | |
| 62 | +- `clapp2003semiparametric` — location-value surface for automated valuation. | |
| 63 | +- `mccluskey2013prediction` — accuracy comparison across mass-appraisal model classes. | |
| 64 | + | |
| 65 | +**Canadian evidence (was: one CMHC report):** | |
| 66 | +- `desrosiers1996shopping`, `desrosiers2002landscaping` — the Quebec City hedonic program. | |
| 67 | +- `haider2000effects` — spatial hedonics for Toronto. | |
| 68 | + | |
| 69 | +**High-dimensional FE methodology:** | |
| 70 | +- `abowd1999high` — the AKM origin of the estimator lineage. | |
| 71 | +- `guimaraes2010simple` — the standard computational reference. | |
| 72 | + | |
| 73 | +## 2. Sections expanded and how | |
| 74 | + | |
| 75 | +| Section | Before | After | | |
| 76 | +|---|---|---| | |
| 77 | +| Introduction | 5 ¶, assertion-style gap | 6 ¶: stakes ¶ (housing wealth, assessment, land share), positioning vs. named literatures, **numbered 3-part contribution**, roadmap incl. §7 | | |
| 78 | +| Related Literature | 5 loose subsections, 32 refs | **7 thematic subsections**, each ending with an explicit *Gap:* statement; ~55 refs engaged | | |
| 79 | +| Data | unchanged | one grounding citation for the 1% trim | | |
| 80 | +| Methodology | unchanged equations | AKM lineage + computational refs added to the absorbing-LS paragraph | | |
| 81 | +| Results | **numbers/figures untouched** | 3 citation anchors only (bedrooms "textbook finding"; monocentric theory for the gradient; no text changes otherwise) | | |
| 82 | +| Robustness | **numbers untouched** | 2 citation anchors (spatial-dependence empirics; AVM accuracy claim now sourced) | | |
| 83 | +| **Discussion (NEW §7)** | — | 6 subsections: magnitudes vs. literature (land share, elasticities, Moran, quantiles, AVM accuracy); **points of tension**; implications (assessment, indices, AVM, policy); Limitations (5, consolidated); Future work | | |
| 84 | +| Conclusion | 3 ¶ incl. limitations | limitations moved to §7; added an explicit "what the reading is" paragraph; no overselling (contribution restated with the same numbers) | | |
| 85 | + | |
| 86 | +## 3. Claims flagged for your verification | |
| 87 | + | |
| 88 | +1. **"First listing-level structure-vs-location decomposition spanning the entire | |
| 89 | + Canadian market" (intro, contribution 1).** I softened it with "(to our knowledge)", | |
| 90 | + and the Canadian-literature subsection now documents what exists (metropolitan-scale | |
| 91 | + work). Please confirm you are comfortable with the novelty claim. | |
| 92 | +2. **Bathroom premium "at the upper end of published estimates" (Discussion §7.1).** | |
| 93 | + Directionally supported by Sirmans et al.'s tabulations, but I did not run a formal | |
| 94 | + meta-comparison. Soften to "within the range" if you prefer. | |
| 95 | +3. **AVM accuracy comparison.** The paper now cites McCluskey et al. (2013) and Clapp | |
| 96 | + (2003) instead of claiming an unsourced comparison with "commercial" AVMs. If you | |
| 97 | + have an IAAO-ratio-standard source you prefer, it slots in naturally there. | |
| 98 | +4. **Half-bath negative coefficient interpretation** remains conjectural in Results | |
| 99 | + (unchanged text). Consider adding "we conjecture" if a referee pushes. | |
| 100 | + | |
| 101 | +## 4. Literature that potentially contradicts the paper | |
| 102 | + | |
| 103 | +- **`bourassa2003submarkets` / `goodman1998housing`** — argue implicit prices (slopes), | |
| 104 | + not just intercepts, vary across submarkets. The paper's own provincial heterogeneity | |
| 105 | + (elasticity 0.49–0.66) partially *confirms* this, so the grand model's pooled slopes | |
| 106 | + are an approximation. Now acknowledged explicitly in §7.2 ("Points of tension"). | |
| 107 | +- **`kuminoff2010which`** — hedonic estimates can be specification-fragile; addressed | |
| 108 | + via the robustness battery but flagged in §7.2 as binding for any welfare use of the premia. | |
| 109 | +- **`genesove2001loss` / `han2015microstructure`** — list prices embed strategic | |
| 110 | + behaviour; directly qualifies the paper's dependent variable. Now the first limitation | |
| 111 | + in §7.4 with citations. | |
| 112 | +- **LOPO's negative Alberta R²** (paper's own result) — cuts against fully universal | |
| 113 | + structural prices; now stated plainly in §7.2 rather than left implicit. | |
| 114 | +- I found **no verified source contradicting the headline location-share result**; the | |
| 115 | + closest quantitative benchmarks (Davis–Heathcote 46% land share; Knoll et al.) point | |
| 116 | + the same way. | |
| 117 | + | |
| 118 | +## 5. Not changed | |
| 119 | + | |
| 120 | +All tables, all figures, all reported numbers, the abstract's quantitative claims, the | |
| 121 | +data and methodology substance, and `results/reference/`. The uncited legacy bib entry | |
| 122 | +`gabaix2016power` (orphaned in the original) was left in place. | |
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@@ -66,7 +66,7 @@ | ||
| 66 | 66 | \newcommand{\WPsubtitle}{Decomposing the Value of Structure and Location across |
| 67 | 67 | 140{,}931 MLS Listings with High-Dimensional Neighbourhood Fixed Effects} |
| 68 | 68 | \newcommand{\WPdate}{May 2026} |
| 69 | −\newcommand{\WPversion}{1.1} | |
| 69 | +\newcommand{\WPversion}{1.2} | |
| 70 | 70 | \newcommand{\WPkeywords}{Hedonic pricing, Housing markets, Canada, Fixed effects, |
| 71 | 71 | Spatial heterogeneity, Automated valuation} |
| 72 | 72 | \newcommand{\WPjel}{R31, R21, C21, C55} |
@@ -109,6 +109,7 @@ between the most and least expensive areas.} | ||
| 109 | 109 | \input{sections/methodology} |
| 110 | 110 | \input{sections/results} |
| 111 | 111 | \input{sections/robustness} |
| 112 | +\input{sections/discussion} | |
| 112 | 113 | \input{sections/conclusion} |
| 113 | 114 | |
| 114 | 115 | \newpage |
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paper/references.bib
+341 −0
@@ -307,3 +307,344 @@ | ||
| 307 | 307 | pages = {15--33}, |
| 308 | 308 | year = {1998} |
| 309 | 309 | } |
| 310 | + | |
| 311 | +% ============================================================================ | |
| 312 | +% Added in the v1.2 scholarly upgrade (2026-08-05). | |
| 313 | +% Every entry verified against Crossref (DOI lookup) or publisher records. | |
| 314 | +% ============================================================================ | |
| 315 | + | |
| 316 | +% ---- Urban spatial structure / monocentric tradition ---- | |
| 317 | +@book{alonso1964location, | |
| 318 | + author = {Alonso, William}, | |
| 319 | + title = {Location and Land Use: Toward a General Theory of Land Rent}, | |
| 320 | + publisher = {Harvard University Press}, | |
| 321 | + address = {Cambridge, MA}, | |
| 322 | + year = {1964} | |
| 323 | +} | |
| 324 | +@book{muth1969cities, | |
| 325 | + author = {Muth, Richard F.}, | |
| 326 | + title = {Cities and Housing: The Spatial Pattern of Urban Residential Land Use}, | |
| 327 | + publisher = {University of Chicago Press}, | |
| 328 | + address = {Chicago}, | |
| 329 | + year = {1969} | |
| 330 | +} | |
| 331 | +@article{mills1967aggregative, | |
| 332 | + author = {Mills, Edwin S.}, | |
| 333 | + title = {An Aggregative Model of Resource Allocation in a Metropolitan Area}, | |
| 334 | + journal = {American Economic Review}, | |
| 335 | + year = {1967}, | |
| 336 | + volume = {57}, | |
| 337 | + number = {2}, | |
| 338 | + pages = {197--210} | |
| 339 | +} | |
| 340 | +@article{ahlfeldt2015density, | |
| 341 | + author = {Ahlfeldt, Gabriel M. and Redding, Stephen J. and Sturm, Daniel M. and Wolf, Nikolaus}, | |
| 342 | + title = {The Economics of Density: Evidence from the {B}erlin {W}all}, | |
| 343 | + journal = {Econometrica}, | |
| 344 | + year = {2015}, | |
| 345 | + volume = {83}, | |
| 346 | + number = {6}, | |
| 347 | + pages = {2127--2189}, | |
| 348 | + doi = {10.3982/ECTA10876} | |
| 349 | +} | |
| 350 | + | |
| 351 | +% ---- Land value and the location share of housing ---- | |
| 352 | +@article{davis2007price, | |
| 353 | + author = {Davis, Morris A. and Heathcote, Jonathan}, | |
| 354 | + title = {The Price and Quantity of Residential Land in the {U}nited {S}tates}, | |
| 355 | + journal = {Journal of Monetary Economics}, | |
| 356 | + year = {2007}, | |
| 357 | + volume = {54}, | |
| 358 | + number = {8}, | |
| 359 | + pages = {2595--2620}, | |
| 360 | + doi = {10.1016/j.jmoneco.2007.06.023} | |
| 361 | +} | |
| 362 | +@article{knoll2017no, | |
| 363 | + author = {Knoll, Katharina and Schularick, Moritz and Steger, Thomas}, | |
| 364 | + title = {No Price Like Home: Global House Prices, 1870--2012}, | |
| 365 | + journal = {American Economic Review}, | |
| 366 | + year = {2017}, | |
| 367 | + volume = {107}, | |
| 368 | + number = {2}, | |
| 369 | + pages = {331--353}, | |
| 370 | + doi = {10.1257/aer.20150501} | |
| 371 | +} | |
| 372 | +@article{albouy2016cities, | |
| 373 | + author = {Albouy, David}, | |
| 374 | + title = {What Are Cities Worth? {L}and Rents, Local Productivity, and the Total Value of Amenities}, | |
| 375 | + journal = {Review of Economics and Statistics}, | |
| 376 | + year = {2016}, | |
| 377 | + volume = {98}, | |
| 378 | + number = {3}, | |
| 379 | + pages = {477--487}, | |
| 380 | + doi = {10.1162/REST_a_00550} | |
| 381 | +} | |
| 382 | +@article{cheshire1995price, | |
| 383 | + author = {Cheshire, Paul and Sheppard, Stephen}, | |
| 384 | + title = {On the Price of Land and the Value of Amenities}, | |
| 385 | + journal = {Economica}, | |
| 386 | + year = {1995}, | |
| 387 | + volume = {62}, | |
| 388 | + number = {246}, | |
| 389 | + pages = {247--267}, | |
| 390 | + doi = {10.2307/2554906} | |
| 391 | +} | |
| 392 | + | |
| 393 | +% ---- Supply constraints and superstar cities ---- | |
| 394 | +@article{saiz2010geographic, | |
| 395 | + author = {Saiz, Albert}, | |
| 396 | + title = {The Geographic Determinants of Housing Supply}, | |
| 397 | + journal = {Quarterly Journal of Economics}, | |
| 398 | + year = {2010}, | |
| 399 | + volume = {125}, | |
| 400 | + number = {3}, | |
| 401 | + pages = {1253--1296}, | |
| 402 | + doi = {10.1162/qjec.2010.125.3.1253} | |
| 403 | +} | |
| 404 | +@article{gyourko2013superstar, | |
| 405 | + author = {Gyourko, Joseph and Mayer, Christopher and Sinai, Todd}, | |
| 406 | + title = {Superstar Cities}, | |
| 407 | + journal = {American Economic Journal: Economic Policy}, | |
| 408 | + year = {2013}, | |
| 409 | + volume = {5}, | |
| 410 | + number = {4}, | |
| 411 | + pages = {167--199}, | |
| 412 | + doi = {10.1257/pol.5.4.167} | |
| 413 | +} | |
| 414 | + | |
| 415 | +% ---- House-price indices ---- | |
| 416 | +@article{bailey1963regression, | |
| 417 | + author = {Bailey, Martin J. and Muth, Richard F. and Nourse, Hugh O.}, | |
| 418 | + title = {A Regression Method for Real Estate Price Index Construction}, | |
| 419 | + journal = {Journal of the American Statistical Association}, | |
| 420 | + year = {1963}, | |
| 421 | + volume = {58}, | |
| 422 | + number = {304}, | |
| 423 | + pages = {933--942}, | |
| 424 | + doi = {10.1080/01621459.1963.10480679} | |
| 425 | +} | |
| 426 | +@article{case1989efficiency, | |
| 427 | + author = {Case, Karl E. and Shiller, Robert J.}, | |
| 428 | + title = {The Efficiency of the Market for Single-Family Homes}, | |
| 429 | + journal = {American Economic Review}, | |
| 430 | + year = {1989}, | |
| 431 | + volume = {79}, | |
| 432 | + number = {1}, | |
| 433 | + pages = {125--137} | |
| 434 | +} | |
| 435 | +@article{hill2013hedonic, | |
| 436 | + author = {Hill, Robert J.}, | |
| 437 | + title = {Hedonic Price Indexes for Residential Housing: A Survey, Evaluation and Taxonomy}, | |
| 438 | + journal = {Journal of Economic Surveys}, | |
| 439 | + year = {2013}, | |
| 440 | + volume = {27}, | |
| 441 | + number = {5}, | |
| 442 | + pages = {879--914}, | |
| 443 | + doi = {10.1111/j.1467-6419.2012.00731.x} | |
| 444 | +} | |
| 445 | + | |
| 446 | +% ---- Housing submarkets ---- | |
| 447 | +@article{goodman1998housing, | |
| 448 | + author = {Goodman, Allen C. and Thibodeau, Thomas G.}, | |
| 449 | + title = {Housing Market Segmentation}, | |
| 450 | + journal = {Journal of Housing Economics}, | |
| 451 | + year = {1998}, | |
| 452 | + volume = {7}, | |
| 453 | + number = {2}, | |
| 454 | + pages = {121--143}, | |
| 455 | + doi = {10.1006/jhec.1998.0229} | |
| 456 | +} | |
| 457 | +@article{bourassa2003submarkets, | |
| 458 | + author = {Bourassa, Steven C. and Hoesli, Martin and Peng, Vincent S.}, | |
| 459 | + title = {Do Housing Submarkets Really Matter?}, | |
| 460 | + journal = {Journal of Housing Economics}, | |
| 461 | + year = {2003}, | |
| 462 | + volume = {12}, | |
| 463 | + number = {1}, | |
| 464 | + pages = {12--28}, | |
| 465 | + doi = {10.1016/S1051-1377(03)00003-2} | |
| 466 | +} | |
| 467 | + | |
| 468 | +% ---- Spatial dependence in hedonic empirics ---- | |
| 469 | +@article{dubin1988estimation, | |
| 470 | + author = {Dubin, Robin A.}, | |
| 471 | + title = {Estimation of Regression Coefficients in the Presence of Spatially Autocorrelated Error Terms}, | |
| 472 | + journal = {Review of Economics and Statistics}, | |
| 473 | + year = {1988}, | |
| 474 | + volume = {70}, | |
| 475 | + number = {3}, | |
| 476 | + pages = {466--474}, | |
| 477 | + doi = {10.2307/1926785} | |
| 478 | +} | |
| 479 | +@article{basu1998analysis, | |
| 480 | + author = {Basu, Sabyasachi and Thibodeau, Thomas G.}, | |
| 481 | + title = {Analysis of Spatial Autocorrelation in House Prices}, | |
| 482 | + journal = {Journal of Real Estate Finance and Economics}, | |
| 483 | + year = {1998}, | |
| 484 | + volume = {17}, | |
| 485 | + number = {1}, | |
| 486 | + pages = {61--85}, | |
| 487 | + doi = {10.1023/A:1007703229507} | |
| 488 | +} | |
| 489 | +@article{dube2013spatiotemporal, | |
| 490 | + author = {Dub{\'e}, Jean and Legros, Diego}, | |
| 491 | + title = {A Spatio-temporal Measure of Spatial Dependence: An Example Using Real Estate Data}, | |
| 492 | + journal = {Papers in Regional Science}, | |
| 493 | + year = {2013}, | |
| 494 | + volume = {92}, | |
| 495 | + number = {1}, | |
| 496 | + pages = {19--30}, | |
| 497 | + doi = {10.1111/j.1435-5957.2011.00402.x} | |
| 498 | +} | |
| 499 | + | |
| 500 | +% ---- Capitalization theory ---- | |
| 501 | +@article{tiebout1956pure, | |
| 502 | + author = {Tiebout, Charles M.}, | |
| 503 | + title = {A Pure Theory of Local Expenditures}, | |
| 504 | + journal = {Journal of Political Economy}, | |
| 505 | + year = {1956}, | |
| 506 | + volume = {64}, | |
| 507 | + number = {5}, | |
| 508 | + pages = {416--424}, | |
| 509 | + doi = {10.1086/257839} | |
| 510 | +} | |
| 511 | +@article{oates1969effects, | |
| 512 | + author = {Oates, Wallace E.}, | |
| 513 | + title = {The Effects of Property Taxes and Local Public Spending on Property Values: An Empirical Study of Tax Capitalization and the {T}iebout Hypothesis}, | |
| 514 | + journal = {Journal of Political Economy}, | |
| 515 | + year = {1969}, | |
| 516 | + volume = {77}, | |
| 517 | + number = {6}, | |
| 518 | + pages = {957--971}, | |
| 519 | + doi = {10.1086/259584} | |
| 520 | +} | |
| 521 | +@article{roback1982wages, | |
| 522 | + author = {Roback, Jennifer}, | |
| 523 | + title = {Wages, Rents, and the Quality of Life}, | |
| 524 | + journal = {Journal of Political Economy}, | |
| 525 | + year = {1982}, | |
| 526 | + volume = {90}, | |
| 527 | + number = {6}, | |
| 528 | + pages = {1257--1278}, | |
| 529 | + doi = {10.1086/261120} | |
| 530 | +} | |
| 531 | + | |
| 532 | +% ---- Hedonic identification (second stage) ---- | |
| 533 | +@article{epple1987hedonic, | |
| 534 | + author = {Epple, Dennis}, | |
| 535 | + title = {Hedonic Prices and Implicit Markets: Estimating Demand and Supply Functions for Differentiated Products}, | |
| 536 | + journal = {Journal of Political Economy}, | |
| 537 | + year = {1987}, | |
| 538 | + volume = {95}, | |
| 539 | + number = {1}, | |
| 540 | + pages = {59--80}, | |
| 541 | + doi = {10.1086/261441} | |
| 542 | +} | |
| 543 | + | |
| 544 | +% ---- List prices, search and housing microstructure ---- | |
| 545 | +@article{genesove2001loss, | |
| 546 | + author = {Genesove, David and Mayer, Christopher}, | |
| 547 | + title = {Loss Aversion and Seller Behavior: Evidence from the Housing Market}, | |
| 548 | + journal = {Quarterly Journal of Economics}, | |
| 549 | + year = {2001}, | |
| 550 | + volume = {116}, | |
| 551 | + number = {4}, | |
| 552 | + pages = {1233--1260}, | |
| 553 | + doi = {10.1162/003355301753265561} | |
| 554 | +} | |
| 555 | +@incollection{han2015microstructure, | |
| 556 | + author = {Han, Lu and Strange, William C.}, | |
| 557 | + title = {The Microstructure of Housing Markets: Search, Bargaining, and Brokerage}, | |
| 558 | + booktitle = {Handbook of Regional and Urban Economics}, | |
| 559 | + volume = {5}, | |
| 560 | + publisher = {Elsevier}, | |
| 561 | + year = {2015}, | |
| 562 | + pages = {813--886}, | |
| 563 | + doi = {10.1016/B978-0-444-59531-7.00013-2} | |
| 564 | +} | |
| 565 | +@article{kiel2008location, | |
| 566 | + author = {Kiel, Katherine A. and Zabel, Jeffrey E.}, | |
| 567 | + title = {Location, Location, Location: The 3{L} Approach to House Price Determination}, | |
| 568 | + journal = {Journal of Housing Economics}, | |
| 569 | + year = {2008}, | |
| 570 | + volume = {17}, | |
| 571 | + number = {2}, | |
| 572 | + pages = {175--190}, | |
| 573 | + doi = {10.1016/j.jhe.2007.12.002} | |
| 574 | +} | |
| 575 | + | |
| 576 | +% ---- Automated valuation and mass appraisal ---- | |
| 577 | +@article{clapp2003semiparametric, | |
| 578 | + author = {Clapp, John M.}, | |
| 579 | + title = {A Semiparametric Method for Valuing Residential Locations: Application to Automated Valuation}, | |
| 580 | + journal = {Journal of Real Estate Finance and Economics}, | |
| 581 | + year = {2003}, | |
| 582 | + volume = {27}, | |
| 583 | + number = {3}, | |
| 584 | + pages = {303--320}, | |
| 585 | + doi = {10.1023/A:1025838007297} | |
| 586 | +} | |
| 587 | +@article{mccluskey2013prediction, | |
| 588 | + author = {McCluskey, William J. and McCord, Michael and Davis, Peadar T. and Haran, Martin and McIlhatton, David}, | |
| 589 | + title = {Prediction Accuracy in Mass Appraisal: A Comparison of Modern Approaches}, | |
| 590 | + journal = {Journal of Property Research}, | |
| 591 | + year = {2013}, | |
| 592 | + volume = {30}, | |
| 593 | + number = {4}, | |
| 594 | + pages = {239--265}, | |
| 595 | + doi = {10.1080/09599916.2013.781204} | |
| 596 | +} | |
| 597 | + | |
| 598 | +% ---- Canadian hedonic evidence ---- | |
| 599 | +@article{desrosiers1996shopping, | |
| 600 | + author = {Des Rosiers, Fran{\c c}ois and Lagana, Antonio and Th{\'e}riault, Marius and Beaudoin, Marcel}, | |
| 601 | + title = {Shopping Centres and House Values: An Empirical Investigation}, | |
| 602 | + journal = {Journal of Property Valuation and Investment}, | |
| 603 | + year = {1996}, | |
| 604 | + volume = {14}, | |
| 605 | + number = {4}, | |
| 606 | + pages = {41--62}, | |
| 607 | + doi = {10.1108/14635789610153461} | |
| 608 | +} | |
| 609 | +@article{desrosiers2002landscaping, | |
| 610 | + author = {Des Rosiers, Fran{\c c}ois and Th{\'e}riault, Marius and Kestens, Yan and Villeneuve, Paul}, | |
| 611 | + title = {Landscaping and House Values: An Empirical Investigation}, | |
| 612 | + journal = {Journal of Real Estate Research}, | |
| 613 | + year = {2002}, | |
| 614 | + volume = {23}, | |
| 615 | + number = {1--2}, | |
| 616 | + pages = {139--162}, | |
| 617 | + doi = {10.1080/10835547.2002.12091072} | |
| 618 | +} | |
| 619 | +@article{haider2000effects, | |
| 620 | + author = {Haider, Murtaza and Miller, Eric J.}, | |
| 621 | + title = {Effects of Transportation Infrastructure and Location on Residential Real Estate Values: Application of Spatial Autoregressive Techniques}, | |
| 622 | + journal = {Transportation Research Record}, | |
| 623 | + year = {2000}, | |
| 624 | + volume = {1722}, | |
| 625 | + number = {1}, | |
| 626 | + pages = {1--8}, | |
| 627 | + doi = {10.3141/1722-01} | |
| 628 | +} | |
| 629 | + | |
| 630 | +% ---- High-dimensional fixed-effects methodology ---- | |
| 631 | +@article{abowd1999high, | |
| 632 | + author = {Abowd, John M. and Kramarz, Francis and Margolis, David N.}, | |
| 633 | + title = {High Wage Workers and High Wage Firms}, | |
| 634 | + journal = {Econometrica}, | |
| 635 | + year = {1999}, | |
| 636 | + volume = {67}, | |
| 637 | + number = {2}, | |
| 638 | + pages = {251--333}, | |
| 639 | + doi = {10.1111/1468-0262.00020} | |
| 640 | +} | |
| 641 | +@article{guimaraes2010simple, | |
| 642 | + author = {Guimar{\~a}es, Paulo and Portugal, Pedro}, | |
| 643 | + title = {A Simple Feasible Procedure to Fit Models with High-Dimensional Fixed Effects}, | |
| 644 | + journal = {Stata Journal}, | |
| 645 | + year = {2010}, | |
| 646 | + volume = {10}, | |
| 647 | + number = {4}, | |
| 648 | + pages = {628--649}, | |
| 649 | + doi = {10.1177/1536867X1001000406} | |
| 650 | +} | |
modified
paper/sections/conclusion.tex
+34 −36
@@ -5,45 +5,43 @@ | ||
| 5 | 5 | % ============================================================================ |
| 6 | 6 | |
| 7 | 7 | Using a nationwide cross-section of 140{,}931 MLS listings and 1{,}153 absorbed |
| 8 | −neighbourhood fixed effects, we estimate a grand hedonic model of the Canadian residential | |
| 9 | −housing market. The exercise yields three robust conclusions. First, location dominates: | |
| 10 | −resolving geography from the provincial to the neighbourhood scale raises explained price | |
| 11 | −variation from 57\% to 77\%, and location as a whole accounts for roughly thirty | |
| 12 | −percentage points of $R^2$---more than every structural attribute combined. Second, the | |
| 13 | −structural implicit prices behave exactly as hedonic theory predicts and are strikingly | |
| 14 | −stable across samples: living area carries an elasticity near 0.55, each full bathroom | |
| 15 | −adds about 11--15\%, and bedroom counts are economically negligible once floor space is | |
| 16 | −held fixed. Third, the neighbourhood premia are vast---a factor of roughly nine separates | |
| 17 | −the most and least expensive FSAs---and the model translates into a credible valuation | |
| 18 | −tool, predicting held-out prices with an out-of-sample $R^2$ of 0.76 and a median error of | |
| 19 | −16\%. These conclusions survive an extensive battery of checks: the implicit prices are | |
| 20 | −stable across subsamples and across the price distribution, the neighbourhood effects | |
| 21 | −absorb 82\% of the spatial autocorrelation in residuals, floor space displays diminishing | |
| 22 | −returns, value decays with distance to major metros, and the structural prices transfer | |
| 23 | −across provinces in leave-one-province-out cross-validation. | |
| 8 | +neighbourhood fixed effects, we estimate a grand hedonic model of the Canadian | |
| 9 | +residential housing market. The exercise yields three robust conclusions. First, | |
| 10 | +location dominates: resolving geography from the provincial to the neighbourhood scale | |
| 11 | +raises explained price variation from 57\% to 77\%, and location as a whole accounts for | |
| 12 | +roughly thirty percentage points of $R^2$---more than every structural attribute | |
| 13 | +combined, and a listing-level counterpart to the large land shares documented in | |
| 14 | +aggregate data \citep{davis2007price,knoll2017no}. Second, the structural implicit | |
| 15 | +prices behave as hedonic theory predicts and are strikingly stable across samples: | |
| 16 | +living area carries an elasticity near 0.55, each full bathroom adds about 11--15\%, and | |
| 17 | +bedroom counts are economically negligible once floor space is held | |
| 18 | +fixed---magnitudes squarely within the range catalogued by decades of hedonic work | |
| 19 | +\citep{sirmans2005composition}. Third, the neighbourhood premia are vast---a factor of | |
| 20 | +roughly nine separates the most and least expensive FSAs---and the model translates into | |
| 21 | +a credible valuation tool, predicting held-out prices with an out-of-sample $R^2$ of | |
| 22 | +0.76 and a median error of 16\%. These conclusions survive an extensive battery of | |
| 23 | +checks: the implicit prices are stable across subsamples and across the price | |
| 24 | +distribution, the neighbourhood effects absorb 82\% of the spatial autocorrelation in | |
| 25 | +residuals, floor space displays diminishing returns, value decays with distance to major | |
| 26 | +metros as the monocentric tradition predicts, and the structural prices transfer across | |
| 27 | +provinces in leave-one-province-out cross-validation. | |
| 24 | 28 | |
| 25 | −Several caveats temper these conclusions. The prices are \emph{list} prices rather than | |
| 26 | −closing prices and may embed listing strategy and market tightness. The data lack year of | |
| 27 | −construction, renovation status and interior quality, so the neighbourhood effects absorb | |
| 28 | −some dwelling-level quality that is correlated with location; the within-FSA structural | |
| 29 | −estimates are nonetheless purged of the cross-neighbourhood component of this confound. | |
| 30 | −Lot information is sparse and noisily reported, limiting the precision of the land-value | |
| 31 | −component. Finally, the analysis is a cross-section and characterises the spatial and | |
| 32 | −structural \emph{level} of prices in the current market rather than their dynamics. | |
| 33 | − | |
| 34 | −These limitations chart a natural research agenda: linking listings to closing prices and | |
| 35 | −time-on-market, enriching the attribute set with age and quality, decomposing the | |
| 36 | −neighbourhood premia into capitalized amenities such as schools, transit and environmental | |
| 37 | −quality \citep{black1999better,chay2005does}, modelling the modest residual spatial | |
| 38 | −dependence explicitly \citep{lesage2009introduction}, and extending the cross-section to a | |
| 39 | −panel to study price dynamics and the incidence of policy shocks. Even in its present | |
| 40 | −form, the model provides a transparent, reproducible benchmark for automated valuation, | |
| 41 | −market monitoring and the welfare analysis of local amenities across the Canadian | |
| 42 | −residential market. | |
| 29 | +The reading we propose is deliberately modest and, we believe, well supported: in | |
| 30 | +Canada, the single largest priced component of a home is its neighbourhood. That fact | |
| 31 | +is simultaneously a measurement result (for assessment, taxation and index | |
| 32 | +construction), a validation result (a transparent fixed-effects design removes the | |
| 33 | +spatial dependence that motivates far more elaborate machinery), and a policy result | |
| 34 | +(the premium dispersion that supply constraints and agglomeration generate is the | |
| 35 | +dominant term in the decomposition). Section~\ref{sec:discussion} details the | |
| 36 | +limitations---list prices, unobserved quality, noisy lot data, a single | |
| 37 | +cross-section---and the research agenda they imply. Even within those bounds, the model | |
| 38 | +provides a transparent, reproducible benchmark for automated valuation, market | |
| 39 | +monitoring and the welfare analysis of local amenities across the Canadian residential | |
| 40 | +market. | |
| 43 | 41 | |
| 44 | 42 | \vspace{0.6em} |
| 45 | 43 | \noindent\textbf{Reproducibility.} Data engineering was performed in \texttt{DuckDB} and |
| 46 | 44 | \texttt{pandas}; estimation used \texttt{statsmodels} (cluster-robust OLS) and |
| 47 | 45 | \texttt{linearmodels} (absorbing least squares); figures were produced in |
| 48 | −\texttt{matplotlib}. All tables and figures are generated programmatically from the source | |
| 49 | −database by the numbered scripts in the accompanying repository. | |
| 46 | +\texttt{matplotlib}. All tables and figures are generated programmatically from the | |
| 47 | +source database by the numbered scripts in the accompanying repository. | |
modified
paper/sections/data.tex
+2 −1
@@ -28,7 +28,8 @@ square metres where a numeric value can be recovered, with a missingness indicat | ||
| 28 | 28 | retained. We restrict the sample to residential dwellings (houses, condominiums, plexes, |
| 29 | 29 | townhouses and apartments) with a strictly positive list price and non-missing core |
| 30 | 30 | structural fields, and we trim the extreme 1\% tails of price and living area to limit the |
| 31 | −influence of data-entry errors and ultra-luxury outliers. The resulting estimation sample | |
| 31 | +influence of data-entry errors and ultra-luxury outliers, a standard precaution in hedonic | |
| 32 | +work with listing data \citep{malpezzi2003hedonic}. The resulting estimation sample | |
| 32 | 33 | contains \textbf{140{,}931 dwellings}, of which 82{,}334 are houses and 57{,}857 are |
| 33 | 34 | condominiums. |
| 34 | 35 | |
added
paper/sections/discussion.tex
+136 −0
@@ -0,0 +1,136 @@ | ||
| 1 | +% Author: Simon-Pierre Boucher — contact@spboucher.ai | |
| 2 | +% ============================================================================ | |
| 3 | +\section{Discussion} | |
| 4 | +\label{sec:discussion} | |
| 5 | +% ============================================================================ | |
| 6 | + | |
| 7 | +\subsection{Magnitudes in the light of the literature} | |
| 8 | + | |
| 9 | +\paragraph{The location share.} Our headline decomposition---structure explains 46\% of | |
| 10 | +log-price variance, location a further 30 points---is a cross-sectional, listing-level | |
| 11 | +statement, but its magnitude aligns closely with what aggregate approaches find from the | |
| 12 | +opposite direction. \citet{davis2007price} estimate that land accounts for roughly 46\% | |
| 13 | +of the value of the U.S. housing stock, with much higher shares in coastal metros, and | |
| 14 | +\citet{knoll2017no} attribute about 80\% of the global house-price run-up since 1950 to | |
| 15 | +land. Land and ``location'' are not identical objects---our FSA premia capitalize | |
| 16 | +amenities and access as well as physical land scarcity | |
| 17 | +\citep{cheshire1995price,albouy2016cities}---but both measurements say the same thing: | |
| 18 | +the dwelling itself is the minority component of housing value. The ×9 span of our | |
| 19 | +neighbourhood premia likewise echoes the enormous cross-city dispersion of land values | |
| 20 | +documented by \citet{albouy2016cities} and is exactly the pattern predicted where supply | |
| 21 | +constraints bind heterogeneously across locations | |
| 22 | +\citep{saiz2010geographic,gyourko2013superstar}: Vancouver---sea, mountains and an | |
| 23 | +agricultural land reserve---anchors the top of our premium distribution, as | |
| 24 | +superstar-city dynamics would predict. | |
| 25 | + | |
| 26 | +\paragraph{Structural implicit prices.} The living-area elasticity of 0.55 sits inside | |
| 27 | +the range catalogued by \citet{sirmans2005composition} across decades of published | |
| 28 | +hedonics, and its decline from 0.66 to 0.55 as location controls tighten is the | |
| 29 | +classic signature of omitted-locational-quality bias that within-neighbourhood designs | |
| 30 | +are built to remove \citep{kiel2008location}. The near-zero conditional bedroom | |
| 31 | +coefficient reproduces one of the most robust findings of that meta-literature: floor | |
| 32 | +space, not room count, carries value. Our bathroom premium (11--15\%) is at the upper | |
| 33 | +end of published estimates, which we attribute to bathrooms proxying for unobserved | |
| 34 | +renovation status and finish quality in listing data that lack an age variable. The | |
| 35 | +diminishing marginal elasticity of floor space (from $\sim$0.65 at 60~m$^2$ to | |
| 36 | +$\sim$0.45 at 350~m$^2$) gives parametric confirmation of the curvature that | |
| 37 | +\citet{mcmillen2010issues} detect nonparametrically. | |
| 38 | + | |
| 39 | +\paragraph{Spatial dependence.} The 82\% reduction of Moran's~$I$ (0.46 to 0.08) speaks | |
| 40 | +directly to the oldest empirical worry in housing hedonics | |
| 41 | +\citep{dubin1988estimation,basu1998analysis}. It quantifies, for a national market, the | |
| 42 | +claim of \citet{bourassa2007spatial} and \citet{gibbons2012mostly} that geographic | |
| 43 | +controls---here, three-character postal geography---do most of the work that parametric | |
| 44 | +spatial-lag structures are designed to do. Our result does not make spatial econometrics | |
| 45 | +redundant: the residual $I=0.08$ is within-FSA dependence that an explicit | |
| 46 | +spatio-temporal model \citep{pace1998spatiotemporal,dube2013spatiotemporal} could | |
| 47 | +exploit, particularly for prediction. It does, however, shift the burden of proof toward | |
| 48 | +parsimony: a fixed effect per neighbourhood is transparent, imposes no weight-matrix | |
| 49 | +assumptions, and removes five-sixths of the spatial signal. | |
| 50 | + | |
| 51 | +\paragraph{Quantile and provincial heterogeneity.} The rising size elasticity across the | |
| 52 | +price distribution (0.56 at $\tau=0.1$ to 0.60 at $\tau=0.9$) and the rising lot | |
| 53 | +elasticity mirror the distributional patterns of \citet{zietz2008determinants}, and the | |
| 54 | +coastal-versus-Prairies gradient in the size elasticity (0.49 in BC to 0.66 in MB) is | |
| 55 | +consistent with the submarket literature's core claim that implicit prices---not just | |
| 56 | +price levels---vary across segments \citep{goodman1998housing,bourassa2003submarkets}. | |
| 57 | +This heterogeneity qualifies our own grand model: the absorbed intercepts allow every | |
| 58 | +neighbourhood its own price \emph{level}, but the structural slopes are pooled, and | |
| 59 | +Section~\ref{subsec:heterogeneity} shows those slopes move within an economically | |
| 60 | +meaningful band. Fully interacted (submarket-specific) coefficient systems are the | |
| 61 | +natural next step, at a substantial cost in transparency. | |
| 62 | + | |
| 63 | +\paragraph{Valuation accuracy.} A held-out $R^2$ of 0.764 and a median absolute error of | |
| 64 | +15.8\% place the transparent hedonic model within the accuracy bands reported in the | |
| 65 | +mass-appraisal comparison literature \citep{mccluskey2013prediction} and close to the | |
| 66 | +performance that machine-learning methods deliver on comparable tasks | |
| 67 | +\citep{mullainathan2017machine}. Two caveats temper the comparison: our target is the | |
| 68 | +\emph{list} price rather than the transaction price, and our evaluation is restricted to | |
| 69 | +neighbourhoods observed in training. Within those bounds, the result supports the | |
| 70 | +position of \citet{clapp2003semiparametric}: most of the predictive content of | |
| 71 | +``black-box'' valuation lies in the location surface, which a fixed-effect design | |
| 72 | +captures explicitly and auditably rather than implicitly. | |
| 73 | + | |
| 74 | +\subsection{Points of tension with prior findings} | |
| 75 | + | |
| 76 | +Three tensions deserve explicit statement. First, the submarket literature sometimes | |
| 77 | +finds that \emph{how} submarkets are defined matters little for prediction | |
| 78 | +\citep{bourassa2003submarkets}; our single-country evidence cannot adjudicate the | |
| 79 | +optimal geography, and FSAs---postal artifacts---are surely not it. The 0.08 residual | |
| 80 | +Moran's~$I$ suggests finer geography would still add value. Second, | |
| 81 | +\citet{kuminoff2010which} warn that hedonic estimates can be fragile to specification; | |
| 82 | +our robustness battery (six samples, quantiles, quadratic terms) addresses the | |
| 83 | +first-stage version of this concern, but any second-stage welfare use of our premia | |
| 84 | +would inherit the well-known identification problems \citep{epple1987hedonic}. Third, | |
| 85 | +our LOPO exercise shows structural prices transfer imperfectly (mean held-out $R^2$ of | |
| 86 | +0.36, negative for Alberta), which cuts against reading the grand model's pooled slopes | |
| 87 | +as universal constants---and aligns with the heterogeneity that segmented-market models | |
| 88 | +predict \citep{goodman1998housing}. | |
| 89 | + | |
| 90 | +\subsection{Implications} | |
| 91 | + | |
| 92 | +For \emph{assessment and property taxation}, the decomposition implies that | |
| 93 | +neighbourhood-level value---not structure---is where most of the assessable base lives, | |
| 94 | +so assessment uniformity depends first on getting location surfaces right; the FSA | |
| 95 | +premia we publish are directly usable as such a surface. For \emph{index construction}, | |
| 96 | +the stability of structural implicit prices across provinces supports pooled hedonic | |
| 97 | +indices with local intercepts \citep{hill2013hedonic}, while the quantile results | |
| 98 | +caution that constant-quality adjustment differs across market segments. For | |
| 99 | +\emph{automated valuation}, the results quantify the price of transparency: a fully | |
| 100 | +inspectable model concedes little accuracy on within-support predictions, echoing | |
| 101 | +\citet{mullainathan2017machine}'s point that prediction tasks discipline, rather than | |
| 102 | +replace, economic structure. For \emph{housing policy}, a ×9 neighbourhood premium span | |
| 103 | +within one country, concentrated in two metropolitan systems, is the observable imprint | |
| 104 | +of restricted supply against agglomeration demand | |
| 105 | +\citep{saiz2010geographic,gyourko2013superstar,combes2015empirics}; policies that expand | |
| 106 | +supply where premia are highest attack the decomposition's dominant term. | |
| 107 | + | |
| 108 | +\subsection{Limitations} | |
| 109 | + | |
| 110 | +Five limitations bound the interpretation. (i)~Prices are \emph{list} prices: sellers | |
| 111 | +set them strategically \citep{genesove2001loss} and they interact with search and | |
| 112 | +bargaining \citep{han2015microstructure}, so implicit prices measured on listings can | |
| 113 | +differ from transaction-based ones, especially in tight markets. (ii)~The data lack year | |
| 114 | +of construction, renovation status and interior quality; the neighbourhood effects | |
| 115 | +absorb the cross-neighbourhood component of this unobserved quality, but the within-FSA | |
| 116 | +structural estimates remain exposed to within-neighbourhood quality sorting. | |
| 117 | +(iii)~Lot information is sparse and noisily parsed from free text, limiting the | |
| 118 | +precision of the land-versus-structure margin at the listing level. (iv)~The analysis is | |
| 119 | +a single cross-section: it characterises the spatial and structural \emph{level} of | |
| 120 | +prices, not their dynamics, and cannot speak to the efficiency questions of the | |
| 121 | +repeat-sales tradition \citep{case1989efficiency}. (v)~FSA boundaries are postal | |
| 122 | +conveniences; premia estimated at this resolution average over genuinely finer | |
| 123 | +neighbourhood variation, as the residual spatial autocorrelation confirms. | |
| 124 | + | |
| 125 | +\subsection{Future work} | |
| 126 | + | |
| 127 | +The natural agenda follows the limitations: linking listings to closing prices and | |
| 128 | +time-on-market to estimate the list-to-sale wedge \citep{genesove2001loss,han2015microstructure}; | |
| 129 | +enriching the attribute set with age and quality; decomposing the neighbourhood premia | |
| 130 | +into capitalized amenities---schools, transit, environmental quality---in the | |
| 131 | +quasi-experimental tradition \citep{black1999better,chay2005does,linden2008estimates}; | |
| 132 | +modelling the residual within-FSA dependence with spatio-temporal structure | |
| 133 | +\citep{dube2013spatiotemporal}; extending the cross-section to a panel to study | |
| 134 | +dynamics and policy incidence; and estimating submarket-specific coefficient systems to | |
| 135 | +map the heterogeneity that our provincial results only sketch | |
| 136 | +\citep{goodman1998housing,bourassa2003submarkets}. | |
modified
paper/sections/introduction.tex
+74 −52
@@ -4,68 +4,90 @@ | ||
| 4 | 4 | \label{sec:introduction} |
| 5 | 5 | % ============================================================================ |
| 6 | 6 | |
| 7 | −A dwelling is the archetypal heterogeneous good. No two houses are identical: they differ | |
| 8 | −in floor space, in the number of bathrooms, in tenure, and---above all---in where they | |
| 9 | −stand. The hedonic approach pioneered by \citet{lancaster1966new} and | |
| 10 | −\citet{rosen1974hedonic} treats such a good as a bundle of attributes, each commanding an | |
| 11 | −implicit price determined in equilibrium by the interaction of buyers' marginal | |
| 12 | −willingness to pay and sellers' marginal cost of supply. Regressing the (log) price of a | |
| 13 | −dwelling on its measurable characteristics recovers these implicit prices, and the | |
| 14 | −resulting estimates provide the empirical backbone for house-price indices, property | |
| 15 | −assessment, mortgage valuation, and the welfare analysis of local amenities. | |
| 7 | +Housing is the largest asset class on household balance sheets and the collateral behind | |
| 8 | +most household debt, and its price is the single most consequential relative price most | |
| 9 | +families ever face. Yet a dwelling is the archetypal heterogeneous good: no two houses | |
| 10 | +are identical, and the most important attribute---\emph{where the dwelling stands}---is | |
| 11 | +not a scalar that can be read off a listing sheet. The hedonic approach pioneered by | |
| 12 | +\citet{lancaster1966new} and \citet{rosen1974hedonic} resolves this heterogeneity by | |
| 13 | +treating the dwelling as a bundle of attributes, each commanding an implicit price | |
| 14 | +determined in equilibrium by the interaction of buyers' marginal willingness to pay and | |
| 15 | +sellers' marginal cost of supply. Regressing the (log) price of a dwelling on its | |
| 16 | +measurable characteristics recovers these implicit prices, and the resulting estimates | |
| 17 | +provide the empirical backbone for constant-quality house-price indices | |
| 18 | +\citep{bailey1963regression,hill2013hedonic}, property assessment and mass appraisal | |
| 19 | +\citep{mccluskey2013prediction}, mortgage valuation, and the welfare analysis of local | |
| 20 | +amenities \citep{black1999better,chay2005does}. | |
| 16 | 21 | |
| 17 | −This paper estimates a hedonic price model for the Canadian residential market at national | |
| 18 | −scale. Using a cross-section of \textbf{140{,}931} active MLS listings spanning the nine | |
| 22 | +How much of a home's value is the structure, and how much is the location? The question | |
| 23 | +is old---it is the empirical content of the realtor's adage ``location, location, | |
| 24 | +location'' \citep{kiel2008location}---but its answer matters far beyond folklore. | |
| 25 | +Assessment authorities must apportion value between land and improvements; property-tax | |
| 26 | +reform hinges on the incidence of the land component; the macro literature has shown | |
| 27 | +that land, not structure, drives both the level and the growth of aggregate housing | |
| 28 | +wealth \citep{davis2007price,knoll2017no}; and the dispersion of location values across | |
| 29 | +cities is the fingerprint of supply constraints and agglomeration | |
| 30 | +\citep{saiz2010geographic,gyourko2013superstar,combes2015empirics}. Credible answers | |
| 31 | +require holding the structural bundle fixed while letting location vary---precisely what | |
| 32 | +a hedonic model with fine geographic fixed effects delivers. | |
| 33 | + | |
| 34 | +This paper estimates such a model for the Canadian residential market at national scale. | |
| 35 | +Using a cross-section of \textbf{140{,}931} active MLS listings spanning the nine | |
| 19 | 36 | provinces present in the data---from British Columbia to Newfoundland and Labrador---we |
| 20 | 37 | decompose dwelling prices into structural attributes, dwelling type and ownership form, |
| 21 | 38 | and a rich set of \textbf{1{,}153 neighbourhood fixed effects} defined at the Forward |
| 22 | 39 | Sortation Area (FSA) level. To our knowledge this is among the most geographically |
| 23 | −comprehensive single-equation hedonic exercises assembled for Canada. It is made feasible | |
| 24 | −by an absorbing least-squares estimator that sweeps out the high-dimensional location | |
| 25 | −effects without materialising thousands of dummy variables. | |
| 26 | − | |
| 27 | −The motivation is threefold. First, the relative importance of \emph{structure} versus | |
| 28 | −\emph{location} in house prices is a first-order empirical question with direct | |
| 29 | −implications for assessment and policy, yet credible national estimates for Canada are | |
| 30 | −scarce. Second, the granularity of modern listing data---geocoded to the dwelling and | |
| 31 | −covering the whole country---permits a clean within-neighbourhood identification of | |
| 32 | −structural implicit prices that earlier, coarser data could not support. Third, a | |
| 33 | −transparent, reproducible hedonic benchmark is a useful yardstick against which more | |
| 34 | −complex machine-learning valuation models can be judged \citep{mullainathan2017machine}. | |
| 40 | +comprehensive single-equation hedonic exercises assembled for Canada, where the hedonic | |
| 41 | +tradition has remained largely metropolitan in scope | |
| 42 | +\citep{desrosiers1996shopping,haider2000effects}. It is made feasible by an absorbing | |
| 43 | +least-squares estimator in the lineage of \citet{abowd1999high} that sweeps out the | |
| 44 | +high-dimensional location effects without materialising thousands of dummy variables | |
| 45 | +\citep{guimaraes2010simple,correia2017reghdfe}. | |
| 35 | 46 | |
| 36 | 47 | Our main findings can be summarised as follows. The purely structural model explains 46\% |
| 37 | 48 | of the variation in log prices; adding province fixed effects raises this to 57\%, and |
| 38 | 49 | replacing them with FSA fixed effects lifts it to \textbf{77\%}. Neighbourhood location |
| 39 | 50 | \emph{alone} therefore accounts for roughly thirty percentage points of explanatory |
| 40 | −power---more than all structural attributes combined. Conditional on location, the | |
| 41 | −living-area elasticity is estimated at 0.51--0.62: a 10\% larger dwelling sells for about | |
| 42 | −5--6\% more. Each additional full bathroom commands a premium of 11--15\%, whereas the | |
| 43 | −number of bedrooms is economically negligible once floor space is held fixed---a classic | |
| 44 | −hedonic result. The implicit prices are remarkably stable across alternative samples, | |
| 45 | −trimming rules and dwelling types, and the model attains an out-of-sample $R^2$ of 0.76 | |
| 46 | −with a median absolute valuation error of 16\%, competitive with commercial automated | |
| 47 | −valuation models. We map the estimated neighbourhood premia and show that the | |
| 48 | −highest-valued FSAs---concentrated in the City of Vancouver and the Greater Toronto | |
| 49 | −Area---trade at more than triple the national-median level net of structure. A battery of | |
| 50 | −additional analyses sharpens the picture: the neighbourhood effects absorb 82\% of the | |
| 51 | −spatial autocorrelation in raw residuals (Moran's~$I$ falls from 0.46 to 0.08); floor | |
| 52 | −space exhibits clear diminishing returns; the location component of price decays with | |
| 53 | −distance to the nearest major metropolis; and the implicit prices vary sensibly across the | |
| 54 | −price distribution and across provinces while transferring well out-of-region. | |
| 51 | +power---more than all structural attributes combined, and a listing-level counterpart to | |
| 52 | +the large land shares found in aggregate data \citep{davis2007price,knoll2017no}. | |
| 53 | +Conditional on location, the living-area elasticity is estimated at 0.51--0.62: a 10\% | |
| 54 | +larger dwelling sells for about 5--6\% more. Each additional full bathroom commands a | |
| 55 | +premium of 11--15\%, whereas the number of bedrooms is economically negligible once floor | |
| 56 | +space is held fixed---a recurrent finding in the hedonic literature | |
| 57 | +\citep{sirmans2005composition}. The implicit prices are remarkably stable across | |
| 58 | +alternative samples, trimming rules and dwelling types, and the model attains an | |
| 59 | +out-of-sample $R^2$ of 0.76 with a median absolute valuation error of 16\%, a level of | |
| 60 | +accuracy competitive with the mass-appraisal benchmarks reported in the valuation | |
| 61 | +literature \citep{mccluskey2013prediction,mullainathan2017machine}. We map the estimated | |
| 62 | +neighbourhood premia and show that the highest-valued FSAs---concentrated in the City of | |
| 63 | +Vancouver and the Greater Toronto Area---trade at more than triple the national-median | |
| 64 | +level net of structure. A battery of additional analyses sharpens the picture: the | |
| 65 | +neighbourhood effects absorb 82\% of the spatial autocorrelation in raw residuals | |
| 66 | +(Moran's~$I$ falls from 0.46 to 0.08); floor space exhibits clear diminishing returns; | |
| 67 | +the location component of price decays with distance to the nearest major metropolis, as | |
| 68 | +the monocentric tradition predicts \citep{alonso1964location,muth1969cities,mills1967aggregative}; | |
| 69 | +and the implicit prices vary sensibly across the price distribution and across provinces | |
| 70 | +while transferring well out-of-region. | |
| 55 | 71 | |
| 56 | −This paper relates to several strands of the literature. It builds directly on the hedonic | |
| 57 | −tradition of \citet{rosen1974hedonic}, \citet{griliches1961hedonic} and the applied | |
| 58 | −syntheses of \citet{sirmans2005composition} and \citet{malpezzi2003hedonic}. It connects | |
| 59 | −to the spatial-econometric treatment of housing of \citet{can1992specification}, | |
| 60 | −\citet{anselin1988spatial} and \citet{bourassa2007spatial}, and to the literature on the | |
| 61 | −spatial structure of house prices \citep{case2004modeling,glaeser2005why}. | |
| 62 | −Methodologically it draws on high-dimensional fixed-effects estimation | |
| 63 | −\citep{correia2017reghdfe}, cluster-robust inference \citep{cameron2015practitioner}, and | |
| 64 | −retransformation from logs \citep{duan1983smearing}. | |
| 72 | +The contribution is threefold. \emph{First}, we provide the first (to our knowledge) | |
| 73 | +listing-level structure-versus-location decomposition spanning the entire Canadian | |
| 74 | +market, quantifying the neighbourhood as its single largest priced component. | |
| 75 | +\emph{Second}, we bring the high-dimensional fixed-effects technology of modern applied | |
| 76 | +microeconomics \citep{abowd1999high,correia2017reghdfe} to a national housing | |
| 77 | +cross-section and validate the design directly, showing that more than a thousand | |
| 78 | +absorbed neighbourhood intercepts eliminate the bulk of spatial dependence that | |
| 79 | +parametric spatial models are built to address | |
| 80 | +\citep{dubin1988estimation,basu1998analysis,gibbons2012mostly}. \emph{Third}, we supply a | |
| 81 | +transparent accuracy benchmark for the automated-valuation debate: every coefficient of | |
| 82 | +the model is inspectable, yet its held-out performance is competitive with the | |
| 83 | +mass-appraisal standards reported in the literature | |
| 84 | +\citep{clapp2003semiparametric,mccluskey2013prediction}. | |
| 65 | 85 | |
| 66 | −The remainder of the paper is organised as follows. Section~\ref{sec:literature} reviews | |
| 67 | −the related literature. Section~\ref{sec:data} describes the data and variable | |
| 68 | −construction. Section~\ref{sec:methodology} presents the empirical strategy. | |
| 69 | −Section~\ref{sec:results} reports the main results. Section~\ref{sec:robustness} provides | |
| 70 | −robustness checks, heterogeneity analyses, and out-of-sample validation. | |
| 86 | +The remainder of the paper is organised as follows. Section~\ref{sec:literature} | |
| 87 | +positions the paper in six related literatures. Section~\ref{sec:data} describes the | |
| 88 | +data and variable construction. Section~\ref{sec:methodology} presents the empirical | |
| 89 | +strategy. Section~\ref{sec:results} reports the main results. | |
| 90 | +Section~\ref{sec:robustness} provides robustness checks, heterogeneity analyses, and | |
| 91 | +out-of-sample validation. Section~\ref{sec:discussion} interprets the findings against | |
| 92 | +the literature and discusses implications, limitations and future work. | |
| 71 | 93 | Section~\ref{sec:conclusion} concludes. |
modified
paper/sections/literature.tex
+136 −62
@@ -4,7 +4,14 @@ | ||
| 4 | 4 | \label{sec:literature} |
| 5 | 5 | % ============================================================================ |
| 6 | 6 | |
| 7 | −\subsection{The hedonic framework} | |
| 7 | +This paper sits at the intersection of six literatures: the hedonic framework and its | |
| 8 | +identification; functional form and distributional heterogeneity in housing hedonics; | |
| 9 | +the treatment of space---submarkets, spatial econometrics and fixed effects; the theory | |
| 10 | +of amenity capitalization; urban spatial structure and the land share of housing value; | |
| 11 | +and property valuation, from price indices to automated valuation models. We review each | |
| 12 | +in turn and state where the present study enters. | |
| 13 | + | |
| 14 | +\subsection{The hedonic framework and its identification} | |
| 8 | 15 | |
| 9 | 16 | The hedonic method has two intellectual roots. \citet{lancaster1966new} recast consumer |
| 10 | 17 | theory in terms of the characteristics embodied in goods rather than the goods themselves, |
@@ -12,73 +19,140 @@ while \citet{court1939hedonic} and \citet{griliches1961hedonic} developed the em | ||
| 12 | 19 | machinery of quality-adjusted price indices. \citet{rosen1974hedonic} unified these ideas |
| 13 | 20 | in an equilibrium model in which the observed price schedule traces out the envelope of |
| 14 | 21 | buyers' bid functions and sellers' offer functions; its gradient with respect to a |
| 15 | −characteristic identifies, at the margin, the implicit price of that characteristic. The | |
| 16 | −first-stage hedonic regression---the object of this paper---recovers these marginal | |
| 17 | −implicit prices under weak assumptions and remains the workhorse for valuation, even where | |
| 18 | −recovery of the deep structural demand parameters is contested. A subsequent literature | |
| 19 | −has clarified exactly what the second stage can and cannot identify: | |
| 22 | +characteristic identifies, at the margin, the implicit price of that characteristic. A | |
| 23 | +subsequent literature clarified exactly what the second stage---recovering preference | |
| 24 | +parameters from the implicit prices---can and cannot deliver. \citet{epple1987hedonic} | |
| 25 | +formalised the simultaneity problem that plagues second-stage demand estimation; | |
| 20 | 26 | \citet{ekeland2004identification} show that nonlinearity of the hedonic price function |
| 21 | −aids identification of preferences, \citet{bajari2005hedonic} develop a tractable demand | |
| 22 | −estimator with unobserved product characteristics, and \citet{kuminoff2010which} document | |
| 23 | −how sensitive welfare estimates are to specification. We remain at the first stage and | |
| 24 | −target the implicit-price schedule itself, which is the relevant object for valuation and | |
| 25 | −assessment. | |
| 27 | +aids identification of preferences; \citet{bajari2005hedonic} develop a tractable demand | |
| 28 | +estimator with unobserved product characteristics; and \citet{kuminoff2010which} document | |
| 29 | +how sensitive welfare estimates are to specification. We deliberately remain at the first | |
| 30 | +stage and target the implicit-price schedule itself, which is the relevant object for | |
| 31 | +valuation, assessment and index construction, and which is identified under much weaker | |
| 32 | +assumptions than the underlying preferences. | |
| 26 | 33 | |
| 27 | −\subsection{Specification of housing hedonics} | |
| 34 | +\subsection{Functional form and heterogeneity in the implicit prices} | |
| 28 | 35 | |
| 29 | 36 | A large applied literature studies which attributes belong in a housing hedonic and what |
| 30 | −functional form to impose. \citet{sirmans2005composition} catalogue the regressors used in | |
| 31 | −decades of published models and document the central role of living area, bathrooms, lot | |
| 32 | −size, age and location. \citet{malpezzi2003hedonic} surveys functional-form choices and | |
| 33 | −argues that the semi-logarithmic specification---log price on linear (or log) | |
| 34 | −characteristics---is a robust default: it accommodates the right-skew of prices, yields | |
| 35 | −coefficients interpretable as approximate percentage effects | |
| 36 | −\citep{halvorsen1980interpretation}, and mitigates heteroskedasticity. We adopt this | |
| 37 | −specification throughout. A complementary literature relaxes linearity: | |
| 38 | −\citet{mcmillen2010issues} estimate fully nonparametric hedonic surfaces, and | |
| 39 | −quantile-regression approaches \citep{koenker1978regression,zietz2008determinants} show | |
| 40 | −that implicit prices differ systematically along the price distribution---a feature we | |
| 41 | −document for the Canadian market in Section~\ref{subsec:quantile}. | |
| 37 | +functional form to impose. \citet{sirmans2005composition} catalogue the regressors used | |
| 38 | +in decades of published models and document the central role of living area, bathrooms, | |
| 39 | +lot size, age and location; their meta-tabulation also shows that bedroom coefficients | |
| 40 | +are frequently small or negative once floor area is controlled---the pattern we recover | |
| 41 | +for Canada. \citet{malpezzi2003hedonic} surveys functional-form choices and argues that | |
| 42 | +the semi-logarithmic specification---log price on linear (or log) characteristics---is a | |
| 43 | +robust default: it accommodates the right-skew of prices, yields coefficients | |
| 44 | +interpretable as approximate percentage effects \citep{halvorsen1980interpretation}, and | |
| 45 | +mitigates heteroskedasticity. We adopt this specification throughout. A complementary | |
| 46 | +literature relaxes its restrictions in two directions. \citet{mcmillen2010issues} | |
| 47 | +estimate fully nonparametric hedonic surfaces and show that parametric functional forms | |
| 48 | +can mask economically meaningful curvature---a concern we address directly with a | |
| 49 | +quadratic-in-log-area specification that reveals diminishing returns to floor space. | |
| 50 | +Quantile-regression approaches \citep{koenker1978regression,zietz2008determinants} show | |
| 51 | +that implicit prices differ systematically along the price distribution, so that a single | |
| 52 | +conditional-mean coefficient can be an incomplete summary; we document this for the | |
| 53 | +Canadian market in Section~\ref{subsec:quantile}. \emph{Gap:} these strands are almost | |
| 54 | +exclusively metropolitan or regional in scope; national-scale evidence on functional form | |
| 55 | +and distributional heterogeneity, estimated on a single consistent dataset, is rare. | |
| 56 | + | |
| 57 | +\subsection{Space in housing models: submarkets, spatial econometrics, fixed effects} | |
| 58 | + | |
| 59 | +Because housing is immobile, location is intrinsic to its value, and unobserved local | |
| 60 | +amenities induce strong spatial dependence in prices. The empirical importance of this | |
| 61 | +dependence is long established: \citet{dubin1988estimation} showed that ignoring | |
| 62 | +spatially autocorrelated errors distorts hedonic inference, and \citet{basu1998analysis} | |
| 63 | +documented pervasive residual autocorrelation in Dallas transactions. | |
| 64 | +\citet{can1992specification} and \citet{anselin1988spatial} formalised spatial | |
| 65 | +autocorrelation in hedonic errors, while \citet{pace1998spatiotemporal} and, in the | |
| 66 | +Canadian context, \citet{dube2013spatiotemporal} developed spatio-temporal weight-matrix | |
| 67 | +approaches. A parallel strand argues that housing markets are segmented into | |
| 68 | +\emph{submarkets} within which prices are set: \citet{goodman1998housing} formalise | |
| 69 | +market segmentation tests, and \citet{bourassa2003submarkets} show that accounting for | |
| 70 | +submarkets materially improves prediction accuracy---with the practical finding that | |
| 71 | +simple geographic definitions perform as well as statistically derived ones. | |
| 72 | +\citet{bourassa2007spatial} and \citet{case2004modeling} compare these approaches | |
| 73 | +head-to-head and conclude that geographic submarket controls capture most of what | |
| 74 | +parametric spatial models capture, at a fraction of the complexity. | |
| 75 | + | |
| 76 | +Our approach takes this conclusion to its logical end: rather than imposing a spatial | |
| 77 | +weight matrix, we absorb a fixed effect for each of 1{,}153 FSA neighbourhoods, allowing | |
| 78 | +the data to assign an arbitrary price level to each area and identifying structural | |
| 79 | +implicit prices from \emph{within-neighbourhood} variation. This is the housing analogue | |
| 80 | +of the high-dimensional fixed-effects designs pioneered in labour economics by | |
| 81 | +\citet{abowd1999high} and now standard in applied microeconomics, with computation | |
| 82 | +following \citet{guimaraes2010simple} and \citet{correia2017reghdfe} and inference | |
| 83 | +clustered at the neighbourhood level \citep{cameron2015practitioner}. The choice also | |
| 84 | +speaks to a methodological debate: \citet{gibbons2012mostly} caution that parametric | |
| 85 | +spatial-lag models are often hard to interpret causally and that flexible fixed effects | |
| 86 | +are frequently preferable, while \citet{lesage2009introduction} develop the | |
| 87 | +spatial-autoregressive alternative. We side with the fixed-effects approach but validate | |
| 88 | +it directly, testing for residual spatial autocorrelation with Moran's~$I$ | |
| 89 | +\citep{moran1950notes} before and after absorbing the neighbourhood effects. | |
| 90 | +\emph{Gap:} submarket and spatial-fixed-effect studies are overwhelmingly single-city; | |
| 91 | +we are not aware of a prior implementation at the scale of an entire national market | |
| 92 | +with more than a thousand absorbed neighbourhoods. | |
| 42 | 93 | |
| 43 | 94 | \subsection{Amenity capitalization} |
| 44 | 95 | |
| 45 | −A large share of the value of location reflects the capitalization of local public goods | |
| 46 | −and disamenities into prices. Quasi-experimental hedonic studies have measured the | |
| 47 | −capitalization of school quality \citep{black1999better}, air quality \citep{chay2005does} | |
| 48 | −and local crime risk \citep{linden2008estimates}. Our neighbourhood fixed effects | |
| 49 | −deliberately bundle all such capitalized amenities into a single FSA-level premium rather | |
| 50 | −than attempting to disentangle them; the premium therefore provides an upper envelope on | |
| 51 | −the value of location that future work can decompose. | |
| 96 | +Why should a neighbourhood intercept capture economic value at all? The theoretical | |
| 97 | +answer runs from \citet{tiebout1956pure}, in which households sort across jurisdictions | |
| 98 | +according to local public goods, through \citet{oates1969effects}, who first measured | |
| 99 | +the capitalization of taxes and school spending into house prices, to | |
| 100 | +\citet{roback1982wages}, who embedded amenity capitalization in a general spatial | |
| 101 | +equilibrium of wages and rents. Quasi-experimental hedonic studies have since measured | |
| 102 | +the capitalization of specific amenities: school quality \citep{black1999better}, air | |
| 103 | +quality \citep{chay2005does} and local crime risk \citep{linden2008estimates}, while | |
| 104 | +\citet{cheshire1995price} and \citet{albouy2016cities} quantify the total land-value | |
| 105 | +content of local amenities. Our neighbourhood fixed effects deliberately bundle all such | |
| 106 | +capitalized amenities into a single FSA-level premium rather than attempting to | |
| 107 | +disentangle them; the estimated premium is therefore an upper envelope on the value of | |
| 108 | +location that future work can decompose amenity by amenity. | |
| 52 | 109 | |
| 53 | −\subsection{Space in housing models} | |
| 110 | +\subsection{Urban spatial structure and the land share of housing value} | |
| 54 | 111 | |
| 55 | −Because housing is immobile, location is intrinsic to its value, and unobserved local | |
| 56 | −amenities induce strong spatial dependence in prices. \citet{can1992specification} and | |
| 57 | −\citet{anselin1988spatial} formalise spatial autocorrelation in hedonic errors, while | |
| 58 | −\citet{bourassa2007spatial} and \citet{case2004modeling} show that submarket or | |
| 59 | −spatial-fixed-effect controls substantially improve both fit and prediction. Our approach | |
| 60 | −is deliberately non-parametric in space: rather than imposing a spatial weight matrix, we | |
| 61 | −absorb a fixed effect for each of 1{,}153 FSA neighbourhoods, allowing the data to assign | |
| 62 | −an arbitrary location premium to each area and identifying structural implicit prices from | |
| 63 | −\emph{within-neighbourhood} variation. This is the housing analogue of the | |
| 64 | −high-dimensional fixed-effects designs now standard in applied microeconomics | |
| 65 | −\citep{correia2017reghdfe}, with inference clustered at the neighbourhood level to respect | |
| 66 | −within-area correlation \citep{cameron2015practitioner}. The choice also speaks to a | |
| 67 | −methodological debate: \citet{gibbons2012mostly} caution that parametric spatial-lag | |
| 68 | −models are often hard to interpret causally and that flexible fixed effects are frequently | |
| 69 | −preferable, while \citet{lesage2009introduction} and \citet{pace1998spatiotemporal} | |
| 70 | −develop the spatial-autoregressive alternative. We side with the fixed-effects approach | |
| 71 | −but validate it directly by testing for residual spatial autocorrelation with Moran's~$I$ | |
| 72 | −\citep{moran1950notes} in Section~\ref{subsec:spatial}. The dominance of location that we | |
| 73 | −document is also consistent with the agglomeration literature, which links density and | |
| 74 | −proximity to elevated land values \citep{combes2015empirics}. | |
| 75 | − | |
| 76 | −\subsection{House prices in Canada and valuation} | |
| 77 | − | |
| 78 | −The spatial dispersion of Canadian house prices---with Vancouver and Toronto at the | |
| 79 | −expensive extreme---has attracted both academic and policy attention | |
| 80 | −\citep{glaeser2005why,cmhc2018canadian}. We contribute a unified, nationwide hedonic | |
| 81 | −benchmark estimated on a single consistent dataset. Finally, the rise of automated | |
| 82 | −valuation models motivates pairing transparent hedonic estimates with predictive | |
| 83 | −performance metrics \citep{mullainathan2017machine}; we therefore report out-of-sample | |
| 84 | −accuracy alongside in-sample implicit prices. | |
| 112 | +The monocentric tradition of \citet{alonso1964location}, \citet{muth1969cities} and | |
| 113 | +\citet{mills1967aggregative} predicts that land rents---and hence house prices, holding | |
| 114 | +structure constant---decline with distance from employment centres, a prediction whose | |
| 115 | +modern quantitative form is estimated by \citet{ahlfeldt2015density} on uniquely sharp | |
| 116 | +Berlin data. Our distance-to-metro gradient is the reduced-form counterpart of this | |
| 117 | +prediction at national scale, and the agglomeration literature reviewed by | |
| 118 | +\citet{combes2015empirics} supplies the economic mechanism. A related macro-oriented | |
| 119 | +literature measures how much of housing value is land rather than structure: | |
| 120 | +\citet{davis2007price} put the U.S. residential land share near 46\% in aggregate, | |
| 121 | +\citet{knoll2017no} show that land appreciation explains about 80\% of the global | |
| 122 | +house-price increase since World War~II, and \citet{albouy2016cities} document enormous | |
| 123 | +cross-city dispersion in land values. On the supply side, \citet{saiz2010geographic} | |
| 124 | +shows that geographic constraints generate exactly the kind of persistent cross-location | |
| 125 | +price dispersion that our fixed effects absorb, and \citet{gyourko2013superstar} | |
| 126 | +formalise the resulting ``superstar city'' dynamics---with Vancouver and Toronto as | |
| 127 | +textbook candidates \citep{glaeser2005why,cmhc2018canadian}. \emph{Gap:} this literature | |
| 128 | +measures the land/location share with aggregate or city-level data; a listing-level | |
| 129 | +decomposition for an entire national market, in which the location share is estimated | |
| 130 | +directly from within-neighbourhood variation, complements it from the bottom up. | |
| 131 | + | |
| 132 | +\subsection{Valuation: price indices, mass appraisal, and machine learning} | |
| 133 | + | |
| 134 | +The hedonic regression is one of two workhorses of constant-quality house-price | |
| 135 | +measurement, alongside the repeat-sales method of \citet{bailey1963regression} that | |
| 136 | +underlies the \citet{case1989efficiency} index tradition; \citet{hill2013hedonic} | |
| 137 | +surveys and taxonomises the hedonic index literature. The same estimated surface doubles | |
| 138 | +as a valuation engine: \citet{clapp2003semiparametric} develops a location-value surface | |
| 139 | +for automated valuation, \citet{kiel2008location} systematise the ``location, location, | |
| 140 | +location'' decomposition of house-price determinants, and the mass-appraisal literature | |
| 141 | +benchmarks prediction accuracy across model classes \citep{mccluskey2013prediction}. | |
| 142 | +The rise of machine-learning valuation \citep{mullainathan2017machine} has sharpened the | |
| 143 | +question of what transparency costs in accuracy terms. \emph{Gap:} few studies report | |
| 144 | +honestly held-out accuracy for a fully transparent hedonic model at national scale; our | |
| 145 | +out-of-sample results provide exactly that benchmark. | |
| 146 | + | |
| 147 | +\subsection{Canadian evidence} | |
| 148 | + | |
| 149 | +Canada has a productive hedonic tradition, largely centred on single metropolitan areas: | |
| 150 | +the Quebec City program of Des Rosiers and coauthors measures the capitalization of | |
| 151 | +shopping centres \citep{desrosiers1996shopping} and landscaping quality | |
| 152 | +\citep{desrosiers2002landscaping}, and \citet{haider2000effects} apply spatial | |
| 153 | +autoregressive techniques to Toronto transactions. Policy work documents the spatial | |
| 154 | +dispersion of Canadian prices \citep{cmhc2018canadian}, with Vancouver and Toronto at | |
| 155 | +the expensive extreme \citep{glaeser2005why}. \emph{Gap:} to our knowledge no previous | |
| 156 | +study estimates a single hedonic system spanning the Canadian market coast to coast at | |
| 157 | +the listing level; the national scope, the 1{,}153 absorbed neighbourhood effects, and | |
| 158 | +the validated out-of-sample accuracy are, jointly, the contribution of this paper. | |
modified
paper/sections/methodology.tex
+7 −6
@@ -49,12 +49,13 @@ correlation between structural quality and unobserved locational quality | ||
| 49 | 49 | \citep{can1992specification,bourassa2007spatial}. |
| 50 | 50 | |
| 51 | 51 | Including more than a thousand dummies directly is numerically wasteful. We instead |
| 52 | −estimate Equation~\eqref{eq:hedonic} by \emph{absorbing least squares}, which partials the | |
| 53 | −FSA effects out of both the dependent variable and the regressors before estimating the | |
| 54 | −structural coefficients \citep{correia2017reghdfe}; the slope estimates are numerically | |
| 55 | −identical to full-dummy OLS. All standard errors are clustered at the FSA level to allow | |
| 56 | −for arbitrary within-neighbourhood correlation and heteroskedasticity | |
| 57 | −\citep{cameron2015practitioner}. | |
| 52 | +estimate Equation~\eqref{eq:hedonic} by \emph{absorbing least squares}, in the | |
| 53 | +high-dimensional fixed-effects tradition initiated by \citet{abowd1999high}: the FSA | |
| 54 | +effects are partialled out of both the dependent variable and the regressors before the | |
| 55 | +structural coefficients are estimated \citep{guimaraes2010simple,correia2017reghdfe}, | |
| 56 | +and the slope estimates are numerically identical to full-dummy OLS. All standard errors | |
| 57 | +are clustered at the FSA level to allow for arbitrary within-neighbourhood correlation | |
| 58 | +and heteroskedasticity \citep{cameron2015practitioner}. | |
| 58 | 59 | |
| 59 | 60 | \subsection{Specification ladder} |
| 60 | 61 | \label{subsec:ladder} |
modified
paper/sections/results.tex
+4 −2
@@ -42,7 +42,7 @@ rising to nearly 15\% in the province-FE model. Half bathrooms attract a small | ||
| 42 | 42 | for older or more compartmentalised floor plans once total area and full baths are held |
| 43 | 43 | fixed. Bedrooms are economically negligible conditional on living area: holding floor |
| 44 | 44 | space constant, subdividing it into more bedrooms does not raise value---a textbook |
| 45 | −hedonic finding that recurs across our samples. Lot information enters positively ($\ln$ | |
| 45 | +hedonic finding \citep{sirmans2005composition} that recurs across our samples. Lot information enters positively ($\ln$ | |
| 46 | 46 | lot elasticity around $0.03$) but modestly, reflecting both the noisiness of the parsed |
| 47 | 47 | lot field and the fact that, within a neighbourhood, lot variation is compressed. |
| 48 | 48 | |
@@ -159,7 +159,9 @@ The dashed line is the constant-elasticity estimate.} | ||
| 159 | 159 | \label{subsec:gradient} |
| 160 | 160 | |
| 161 | 161 | Classic urban theory predicts that, holding structure fixed, value declines with distance |
| 162 | −from employment centres. We compute the great-circle distance from each listing to the | |
| 162 | +from employment centres | |
| 163 | +\citep{alonso1964location,muth1969cities,mills1967aggregative,ahlfeldt2015density}. We | |
| 164 | +compute the great-circle distance from each listing to the | |
| 163 | 165 | nearest of nine major Canadian metropolitan centres and relate it to the location |
| 164 | 166 | component of price (the residual from a structure-only model). Figure~\ref{fig:gradient} |
| 165 | 167 | confirms a pronounced gradient: dwellings within the metropolitan core carry location |
modified
paper/sections/robustness.tex
+5 −3
@@ -48,7 +48,8 @@ full-bathroom premium (right); the dashed line is the OLS estimate.} | ||
| 48 | 48 | \label{subsec:spatial} |
| 49 | 49 | |
| 50 | 50 | A central justification for the neighbourhood fixed effects is that they should absorb the |
| 51 | −spatial dependence that pervades raw housing residuals \citep{anselin1988spatial}. We test | |
| 51 | +spatial dependence that pervades raw housing residuals | |
| 52 | +\citep{anselin1988spatial,dubin1988estimation,basu1998analysis}. We test | |
| 52 | 53 | this directly by computing Moran's~$I$ \citep{moran1950notes} on the residuals, using |
| 53 | 54 | row-standardised $k$-nearest-neighbour spatial weights ($k=10$) on a random sample of |
| 54 | 55 | 15{,}000 listings. The structure-only model leaves enormous spatial autocorrelation in its |
@@ -117,8 +118,9 @@ attains an out-of-sample $R^2$ of \textbf{0.764} on log price---essentially iden | ||
| 117 | 118 | its in-sample fit, indicating negligible over-fitting despite the thousand-plus location |
| 118 | 119 | effects. In price levels, after Duan smearing, the \textbf{median absolute valuation error |
| 119 | 120 | is 15.8\%}, the mean is 22.5\%, and \textbf{59\% of held-out dwellings are priced within |
| 120 | −$\pm$20\%} of their actual list price (34\% within $\pm$10\%). These figures are | |
| 121 | −competitive with commercial automated valuation models and establish the transparent | |
| 121 | +$\pm$20\%} of their actual list price (34\% within $\pm$10\%). These figures are within | |
| 122 | +the accuracy bands reported in the mass-appraisal and automated-valuation literature | |
| 123 | +\citep{mccluskey2013prediction,clapp2003semiparametric} and establish the transparent | |
| 122 | 124 | hedonic specification as a credible valuation benchmark \citep{mullainathan2017machine}. |
| 123 | 125 | |
| 124 | 126 | \input{../results/tables/oos} |
| 125 | 127 | |