Abstract
This paper examines the principle-agency problem between landlords and real estate agents using novel data on rental contracts. Real estate agents are found to obtain higher contract rents by approximately 1% more for themselves (and family members) than for other landlords, which is economically small. The results suggest that the principle-agency program with real estate agents is less of a concern in the rental market than the ownership market. The reason potentially relates to the commission structure, the relatively low effort associated with finding a tenant, the landlord’s ability to evaluate an agent’s performance, and reputation concerns from repeated interactions.
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For instance, Lopez and Yoshida (2021) point out that about one out of every five non-commercial residential units in Las Vegas show up in the rental MLS platform, suggesting that many homeowners lease property without using a real estate agent. On the other hand, the National Association of Realtors, 2016 reports that more than 88% of buyers purchased their homes using a real estate agent.
Private platforms such as Redfin do not send data on rental listings to other competing platforms like Zillow. Moreover, rental platforms may require landlords to sign exclusive rental listing agreements that bar landlords from using multiple rental platforms simultaneously, and therefore, constrain the number of potential tenants viewing the property.
Exceptions may include landlords who are temporarily relocating or are in other situations in which they may be less concerned absolute getting the absolute highest rent possible and more interested in shielding against homeownership costs. However, over 94% of the rentals in the sample are vacant or tenant occupied and not owner occupied, suggesting that most rentals were placed on the market for investment purposes.
The Las Vegas Realtors were previously known as the Greater Las Vegas Association of Realtors (GLVAR). The rental MLS dataset contains about 150,000 unique rental properties, representing about 22% of all the unique non-commercial residential properties recorded in the Clark County Assessor Office as of March 2019. Lopez and Yoshida (2021) also examine these data on rental contracts from the MLS.
The reason that vacancy is at 92% is an empirical fact whose determinants will be left for future research.
Note that time-on-market and the cap rate are winsorized at the 1% tails.
Unfortunately, I do not observe operating expenditures or revenue ex-post lease, which makes it difficult to estimate the actual capitalization rate without using ad hoc assumptions.
See https://addictedrealty.com/wp-content/uploads/2018/01/GLVAR-MLS-Policies-August-2016.pdf. An individual may look up a Nevada real estate license using the following website: https://red.prod.secure.nv.gov/Lookup/LicenseLookup.aspx
Landlords who are unrelated to the real estate agent but personally affiliated to another real estate licensee perhaps under-report the said affiliation in which case fewer than the true number of agent-related rental properties would be identified and bias the analysis towards finding little differences in the market outcomes between agent-related and arm’s-length rental properties.
Later in the analysis, agent-owned or agent-related properties are matched to arm’s-length properties using propensity score matching to reduce concerns about examining unbalanced groups of properties.
If the agent-owned or agent-related status is under-reported, then coefficient estimates of \(\delta _{1}\) and \(\delta _{2}\) would be biased towards zero since the control sample would include rentals that are truly agent-owned and agent-related. However, this bias is unlikely as discussed in Section 3.
Note that for categorical variables, the largest class is set as the base category.
Year-quarter-zip fixed effects do not materially affect the principal results. Subdivisions are more granular delineation of neighborhoods than census tracts and zip codes, including condominiums.
For example, as discussed and examined in Section 5, rental properties that generate multiple rental contracts in the sample tend to be held by large or corporate landlords, while properties with one rental contract in the sample tend to be owned by small or individual landlords.
In the appendix, Table A.1 controls for the rental contract term length non-linearly; the results are identical to the baseline estimates. Table A.2 shows that the main results hold within property type subsamples. Consistent results also arise when using the monthly rent per square foot as the dependent variable (see Table A.3). Furthermore, the results remain unchanged when using listing year-month fixed effects instead of listing year-quarter fixed effects, suggesting that the baseline estimates of the agent-owned and agent-related premiums are robust to possible within-quarter seasonal effects.
Cohen’s d-statistic is measured as the mean difference between the treatment group and control group divided by the pooled standard deviation. Generally, a d-statistic is considered small and economically meaningless if its absolute value is (or less than) 0.2 (see Cohen, 1977).
\(\$499 = 0.003 \times \$1,290 \times 12 / 9.3\%\); \(\$1,115 = 0.0067 \times \$1,290 \times 12 / 9.3\%\)
Lopez (2021) employs a similar strategy.
The small sample size of agent-related listings introduces volatility to the point estimates of the agent-related premium.
I define a household as an individual or group of individuals that is not a fictitious entity such as a trust or corporation using the “grantee” variable and by flagging observations that do not have abbreviations or key words such as “LLC”, “Inc”, and “Trust”.
See for example Agarwal et al. (2019) who use the sales price to listing price ratio as a proxy for bargaining effort.
For expired/withdrawn listings, I set a similar set of filters to those reported in Section 3 for leased listings.
Following concerns that TOM may be constructed differently depending on whether withdrawn or expired listings are in the sample (Benefield & Hardin, 2015), I find similar results when measuring TOM as the number of days between the “off-the-market” date and listing date and including withdrawn or expired listings in the sample.
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I thank Sumit Agrawal, Dominique Badoer, Itzhak Ben-David, Walter D’Lima, Yulia Demyanyk, Joan Ferre-Mensa, Erasmo Giambona, John Graham, Jacob Sagi, Ruchi Singh, Rohan Williamson and seminar participants at the Financial Management Association International 2020 Diversity Emerging Scholars Initiative for helpful comments and suggestions. I also thank the Nevada Real Estate Division, Clark County Assessor Office, and LIED Institute for Real Estate Studies at the University of Nevada Las Vegas for providing data.
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Lopez, L.A. Is there a Principal-Agency Problem with Real Estate Agents in Rental Markets?. J Real Estate Finan Econ (2022). https://doi.org/10.1007/s11146-022-09927-8
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DOI: https://doi.org/10.1007/s11146-022-09927-8