Real Estate Research

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Real Estate Research provides analysis of topical research and current issues in the fields of housing and real estate economics. Authors for the blog include the Atlanta Fed's Kristopher Gerardi, Carl Hudson, and analysts, as well as the Boston Fed's Christopher Foote and Paul Willen.


May 20, 2015


Are Millennials Responsible for the Decline in First-Time Home Purchases?

First-time homebuyers play a critical role in the housing market because they allow existing homebuyers to sell their homes and trade up, triggering a cascade of home sales. While their share of all purchases has remained fairly flat over time (see our previous post on this topic), the number of first-time homebuyers has declined precipitously since the real estate crash. Many think of first-time homebuyers as younger households, and believe millennials are largely behind the decline in first-time homebuying. There are a variety of theories about why millennials have been slow to enter homeownership. One theory says that millennials would rather rent in dense urban areas where land is scarce than buy homes in the suburbs. Another theory blames steep increases in student debt for crowding out mortgage debt and reducing the homeownership opportunities of younger generations. Yet another theory argues that because the recession lowered incomes, younger people can't afford to buy. Finally, underwriting standards tightened after the recession, causing mortgage lenders to require larger down payments and higher credit scores in order to buy a home. Some worry that this more stringent lending environment has raised the bar too high for millennial homebuyers in particular.

We can't examine all these theories in a blog post, but we can examine the validity of the assumption that millennials are driving the decline in first-time homebuyers. We approached this from two angles. We first looked at whether the age distribution of first-time homebuyers has changed, and then we tried to discern patterns in first-time home buying across states. In general, we find that the age distribution of first-time homebuyers has become younger, not older, since the crisis. We also found that the dramatic fall in purchases varies much more strongly across states than by age. The preliminary figures suggest that housing market and local economic conditions may explain as much or more of the decline in first-time homebuyers than a generational divide.

Searching the data for first mortgages
Our analysis is based on the Federal Reserve Bank of New York Consumer Credit Panel. This data set provides longitudinal, individual data, using a 5 percent sample of all persons with a credit record and social security number in the United States.i We examined the age, location, and credit scores of people who bought homes for the first time and looked at how these characteristics changed after the crisis.ii

To identify first-time homebuyers, we flagged the first year of the oldest mortgage for each individual in the credit panel. This reveals the first instance of someone obtaining a mortgage, even if they subsequently buy another home or even transition back to renting. The trade-off is we were able to observe only those who use debt finance, and thereby excluded all cash purchases. While many homeowners do own their homes outright, we expect most first-time buyers and certainly most young buyers to have a mortgage.iii

Having isolated first-time homebuyers in this data set, we looked at their purchasing trends and demographic attributes from 2000 to 2014. In this data set, we found that roughly 1 percent to 2 percent of the population purchased a mortgage-financed home for the first time in a given year. Forty-nine percent to 53 percent had no mortgage (this category combines renters and those who own their homes outright), and 45 percent to 50 percent were paying down an existing mortgage.

Percent-of-individuals

Buyers aren't getting older
We found that the number of first-time home buyers fell precipitously after the crash, from 3.3 million a year to around 1.5 million to 1.8 million. However, the age distribution of these first-time homebuyers does not change dramatically, though the median age of actually went down slightly since the peak. If we were to believe that the decline in first-time buyers was driven primarily by younger workers requiring more time to amass a down payment or pay off student debts, then we would expect to see first-time buyers getting older.

First-time-homebuyers

We did not see a strong explanation for dramatic declines in first-time homebuyers when we compared younger and older adults. It doesn't appear that millennials are driving the decline. By comparison, when we reviewed the number of first-time home purchases by state, we found very dramatic differences that population alone cannot explain. Unsurprisingly, first-time homebuying fell further in places where the housing crisis hit the hardest.

The chart shows the number and percent change in first-time homebuyers from 2001 to 2011 by state. There is a wide variety in the percent change in first-time homebuyers, with declines as strong as 65 percent in some states and as low as 10 percent in others. North Dakota was the only state to have increases in first-time homebuyers, likely due to the oil industry growth there.

Change-in-first-time-home-buyers

This analysis does have some weaknesses. For one, as we mentioned, it omits cash buyers, who are an increasingly important segment of the housing market, especially in hard-hit states like Georgia and Florida. Also, other research has shown that the transition from renter to owner and back can happen many times in a person's lifetime, and this data set does not control for homeownership "spells" older than one year (see Boehn and Schlottman 2008). Notwithstanding, this analysis suggests that the decline in first-time homebuying is driven not by swiftly changing preferences nor the economic constraints of the younger generation but by regional and local economic conditions. Stay tuned for more, as we plan to look further into how the real estate crisis altered the home purchase decisions of young first-time homebuyers relative to older generations.

Photo of Carl Hudson By Elora Raymond, graduate research assistant, Center for Real Estate Analytics in the Atlanta Fed's research department, and doctoral student, School of City and Regional Planning at the Georgia Institute of Technology, and

Photo of Jessica DillJessica Dill, economic policy analysis specialist in the Atlanta Fed's research department

_______________________________________

i The data is a 2.5 percent sample of all individuals with a credit history in the United States. So, for example, this sample resulted in 636,638 records in 2014, which would correspond to an estimated 254,655,200 individuals with credit records and social security numbers in 2014.

ii We excluded anyone who had an older mortgage in a prior year. Doing so resulted in only a very small percentage of records being excluded.

iii Our approach and results are similar to those cited in Agarwal, Hu, and Huang (2014), who find that the homeownership rate between 1999 and 2012 varies between 44 percent and 47 percent for individuals aged 25—60 using a different time frame and age distribution of the same data set. Because our definition—and that of Agarwal, Hu, and Huang—is unique, it differs from the widely cited homeownership rate published by the U.S. Census Bureau. The rate published by the Census Bureau ranges between 65 and 68 percent for individuals over 25 years old and is calculated by dividing the number of owner-occupied households by the total number of occupied households. Homeownership rates have also been derived using other data. Gicheva and Thompson (2014) derive a homeownership rate using the Survey of Consumer Finance and find the mean homeownership rate to be 61 percent between 1995 and 2010. Gerardi, Rosen, and Willen (2007) used the Panel Survey of Income Dynamics (PSID), which tracks households over time and captures changes in tenure status, to identify home purchasers. They reported a range of 5.6 percent (in 1983) to 9.6 percent (in 1978) of households buying homes in the 1969—99 timeframe.

May 20, 2015 in Financial crisis, Homeownership, Housing boom, Housing crisis | Permalink | Comments (0)

April 20, 2015


Income Growth, Credit Growth, and Lending Standards: Revisiting the Evidence

Almost a decade has passed since the peak of the housing boom, and a handful of economics papers have emerged as fundamental influences on the way that economists think about the boom—and the ensuing bust. One example is a paper by Atif Mian and Amir Sufi that appeared in the Quarterly Journal of Economics in 2009 (MS2009 hereafter). A key part of this paper is an analysis of income growth and mortgage-credit growth in individual U.S. ZIP codes. The authors find that from 2002 to 2005, ZIP codes with relatively low growth in incomes experienced high growth in mortgage credit; that is, income growth and credit growth were negatively correlated during this period.

Economists often cite this negative correlation as evidence of improper lending practices during the housing boom. The thinking is that prudent lenders would have generated a positive correlation between area-level growth in income and mortgage credit, because borrowers in ZIP codes with high income growth would be in the best position to repay their loans. A negative correlation suggests that lenders instead channeled credit to borrowers who couldn't repay.

Some of the MS2009 results are now being reexamined in a new paper by Manuel Adelino, Antoinette Schoar, and Felipe Severino (A2S hereafter). The A2S paper argues that the statistical evidence in MS2009 is not robust and that using borrower-level data, rather than data aggregated up to the ZIP-code level, is the best way to investigate lending patterns. The A2S paper has already received a lot of attention, which has centered primarily on the quality of the alternative individual-level data that A2S sometimes employ.1 To understand the relevant issues in this debate, it's helpful to go back to MS2009's original statistical work that uses data aggregated to the ZIP-code level to get a sense of what it does and doesn't show.

Chart 1: Measures of the Relationship between within-County Income Growth and Credit Growth for U.S. ZIP Codes

Chart 1 summarizes the central MS2009 result. We generated this chart from information we found in either MS2009 or its supplementary online appendix. The dark blue bars depict the coefficients from separate regressions of ZIP-code level growth in new purchase mortgages on growth in ZIP-code level incomes.2 (These regressions also include county fixed effects, which we discuss further below.) Each regression corresponds to a different sample period. The first regression projects ZIP-level changes in credit between 1991 and 1998 on ZIP-level changes in income between these two years. The second uses growth between 1998 and 2001, and so on.3 During the three earliest periods, ZIP-level income growth enters positively in the regressions, but in 2002–04 and 2004–05, the coefficients become negative. A key claim of MS2009 is that this flip signals an important and unwelcome change in the behavior of lenders. Moreover, the abstract points out that the negative coefficients are anomalous: "2002 to 2005 is the only period in the past eighteen years in which income and mortgage credit growth are negatively correlated."

Chart 2: Serious Delinquency Rates by Loan Vintage

There are, however, at least three reasons to doubt that the MS2009 coefficients tell us anything about lending standards. First of all, the coefficients for the 2005–06 and 2006–07 regressions are positive—for the latter period, strongly so. By MS2009's logic, these positive coefficients indicate that lending standards improved after 2005, but in fact loans made in 2006 and 2007 were among the worst-performing loans in modern U.S. history. Chart 2 depicts the share of active loans that are 90-plus days delinquent or in foreclosure as a share of currently active loans, using data from Black Knight Financial Services. To be sure, loans made in 2005 did not perform well during the housing crisis, but the performance of loans made in 2006 and 2007 was even worse.4 This poor performance is not consistent with the improvement in lending standards implied by MS2009's methodology.

A second reason that sign changes among the MS2009 coefficients may not be informative is that these coefficients are not really comparable. The 1991–98 regression is based on growth in income and credit across seven years, while later regressions are based on growth over shorter intervals. This difference in time horizon matters, because area-level income and credit no doubt fluctuate from year to year while they also trend over longer periods. A "high-frequency" correlation calculated from year-to-year growth rates may therefore turn out to be very different from a "low-frequency" correlation calculated by comparing growth rates across more-distant years. One thing we can't do is think of a low-frequency correlation as an "average" of high-frequency correlations. Note that MS2009 also run a regression with growth rates calculated over the entire 2002–05 period, obtaining a coefficient of -0.662. This estimate, not pictured in our graph, is much larger in absolute value than either of the coefficients generated in the subperiods 2002–04 and 2004–05, which are pictured.

A third and perhaps more fundamental problem with the MS2009 exercise is that the authors do not report correlations between income growth and credit growth but rather regression coefficients.5 And while a correlation coefficient of 0.5 indicates that income growth and credit growth move closely together, a regression coefficient of the same magnitude could be generated with much less comovement. MS2009 supply the data needed to convert their regression coefficients into correlation coefficients, and we depict those correlations as green bars in chart 1.6 Most of the correlations are near 0.1 in absolute value or smaller. To calculate how much comovement these correlations imply, recall that the R-squared of a regression of one variable on another is equal to the square of their correlation coefficient. A correlation coefficient of 0.1 therefore indicates that a regression of credit growth deviated from county-level means on similarly transformed income growth would have an R-squared in the neighborhood of 1 percent. The reported R-squareds from the MS2009 regressions are much larger, but that is because the authors ran their regressions without demeaning the data first, letting the county fixed effects do the demeaning automatically. While this is standard practice, this specification forces the reported R-squared to encompass the explanatory power of the fixed effects. The correlation coefficients that we have calculated indicate that the explanatory power of within-county income growth for within-county credit growth is extremely low.7 Consequently, changes in the sign of this correlation are not very informative.

How do these arguments relate to A2S's paper? Part of that paper provides further evidence that the negative coefficients in the MS2009 regressions do not tell us much about lending standards. For example, A2S extend a point acknowledged in MS2009: expanding the sample of ZIP codes used for the regressions weakens the evidence of a negative correlation. The baseline income-credit regressions in MS2009 use less than 10 percent of the ZIP codes in the United States (approximately 3,000 out of more than 40,000 total U.S. ZIP codes). Omitted from the main sample are ZIP codes that do not have price-index data or that lack credit-bureau data.8 MS2009 acknowledge that if one relaxes the restriction related to house-price data, the negative correlations weaken. Our chart 1 conveys this information with the correlation coefficients depicted in red, which are even closer to zero. A2S go farther to show that if the data set also includes ZIP codes that lack credit-bureau data, the negative correlation and regression coefficients become positive.

But perhaps a deeper contribution of A2S is to remind the researchers that outstanding questions about the housing boom should be attacked with individual-level data. No one doubts that credit expanded during the boom, especially to subprime borrowers. But how much of the aggregate increase in credit went to subprime borrowers, and how did factors like income, credit scores, and expected house-price appreciation affect both borrowing and lending decisions? Even under the best of circumstances, it is hard to study these questions with aggregate data, as MS2009 did. People who take out new-purchase mortgages typically move across ZIP-code boundaries. Their incomes and credit scores may be different than those of the people who lived in their new neighborhoods one, two, or seven years before. A2S therefore argue for the use of HMDA individual-level income data so that credit allocation can be studied at the individual level. This use has been criticized by Mian and Sufi, who believe that fraud undermines the quality of the individual-level income data that appear in HMDA records. We should take these criticisms seriously. But the debate over whether lending standards are best studied with aggregate or individual-level data should take place with the understanding that aggregate data on incomes and credit may not be as informative as previously believed.

1 Mian and Sufi's contribution to the data-quality debate can be found here.

2 Data on new-purchase mortgage originations come from records generated by the Home Mortgage Disclosure Act (HMDA). Average income at the ZIP-code level is tabulated in the selected years by the Internal Revenue Service.

3 Growth rates used in the regressions are annualized. The uneven lengths of the sample periods are necessitated by the sporadic availability of the IRS income data, especially early on. The 1991 data are no longer available because IRS officials have concerns about their quality.

4 Chart 2 includes data for both prime and subprime loans. The representativeness of the Black Knight/LPS data improves markedly in 2005, so LPS loans originated before that year may not be representative of the universe of mortgages made at the same time. For other evidence specific to the performance of subprime loans made in 2006 and 2007, see Figure 2 of Christopher Mayer, Karen Pence, and Shane M. Sherlund, "The Rise in Mortgage Defaults," Journal of Economic Perspectives (2009), and Figure 1 of Yuliya Demyanyk and Otto Van Hemert, "Understanding the Subprime Mortgage Crisis," Review of Financial Studies (2009). For data on the performance of GSE loans made in 2006 and 2007, see Figure 8 of W. Scott Frame, Kristopher Gerardi, and Paul S. Willen, "The Failure of Supervisory Stress Testing: Fannie Mae, Freddie Mac, and OFHEO," Atlanta Fed Working Paper (2015).

5 MS2009 often refer to their regression coefficients as "correlations" in the text as well as in the relevant tables and figures, but these statistics are indeed regression coefficients. Note that in the fourth table of the supplemental online appendix, one of the "correlations" exceeds 1, which is impossible for an actual correlation coefficient.

6 Because a regression coefficient from a univariate regression is Cov(X,Y)/Var(X), multiplying this coefficient times StdDev(X)/StdDev(Y) gives Cov(X,Y)/StdDev(X)*StdDev(Y), which is the correlation coefficient. Here, the Y variable is ZIP-code–level credit growth, demeaned from county-level averages, while X is similarly demeaned income growth. As measures of the standard deviations, we use the within-county standard deviations displayed in Table I of MS2009. Specifically, we use the within-county standard deviation of "mortgage origination for home purchase annual growth" calculated over the 1996–02 and 2002–05 periods (0.067 and 0.15, respectively) and the within-county standard deviation of "income annualized growth" over the 1991–98, 1998–2002, 2002–05, and 2005–06 periods (0.022, 0.017, 0.031, and 0.04, respectively). Unfortunately, the time periods over which the standard deviations were calculated do not line up exactly with the time periods over which the regression coefficients were calculated, so our conversion to correlation coefficients is an approximation.

7 It is true that the regression coefficients in the MS2009 coefficients often have large t-statistics, so one may argue that ZIP-level income growth has sometimes been a statistically significant determinant of ZIP-level credit growth. But the low correlation coefficients indicate that income growth has never been economically significant determinant of credit allocation within counties. It is therefore hard to know what is driving the income-credit correlation featured in MS2009, or what may be causing its sign to fluctuate.

8 Though house prices and credit bureau data are not required to calculate a correlation between income growth and mortgage-credit growth, the authors use house prices and credit bureau data in other parts of their paper.


April 20, 2015 in Credit conditions, Housing boom, Housing crisis, Mortgage crisis, Subprime mortgages | Permalink | Comments (0)

March 25, 2015


Where Is the Credit Availability Pendulum Now? (Part 2 of 2)

In our previous post, we considered survey-based and index measures of mortgage credit availability. We concluded that availability has slowly but steadily been improving since early 2013. In this post, we focus on borrower characteristics for originated mortgages. We think of availability of credit as the willingness of lenders to lend while borrower characteristics shape the quantity of purchasers that are qualified to buy. By turning to mortgage origination data, we can look at the “credit box” and track changes (that is, expansions and contractions) in the credit box over time. We do this acknowledging that this approach fails to capture variation in loans that have been declined and allows us only to observe variation in loans that have been originated.

Looking at trends in credit characteristics of purchase mortgages originations, we find data that support the idea that the credit box, which tightened during the Great Recession, has not gotten looser. For one, the distribution of FICO scores on conventional mortgages shifted during the housing downturn to a distribution dominated by borrowers with higher credit scores—those above 680—and has yet to show much movement in the other direction.

Distribution-of=credit-scores

Yet credit scores represent just one dimension of a multidimensional credit box. To paint a fuller picture, consider loan-to-value (LTV) ratios before and after the housing downturn. The table shows summary statistics of this data. Comparing the distributions of LTV ratios of mortgages originated in 2006 and 2014, it seems somewhat counterintuitive that the share of conventional mortgages with high LTVs was greater in 2014 (35.3 percent) than in 2006 (21.2 percent).

150325-table

Layering the distribution of FICO scores on the distribution of LTVs helps to explain away some of this peculiarity. A sizable share of the 2006 loans that were originated with an LTV greater than 80 percent fell on the lower end of the credit score spectrum. In contrast, most of the loans originated in 2014 with LTVs greater than 80 percent fell on the higher end of the credit score distribution.

One thing that is not in our data set is the extent to which these mortgages had piggyback mortgages. Data provided by Inside Mortgage Finance indicates that second-mortgage originations decreased from $430 billion in 2006 to $59 billion in 2013 (the most recent year for which data are available). That is, seconds shrank from 14 percent of total originations to just 3 percent of total originations. So it is possible that the share of conventional mortgages with an LTV greater than 80 percent is understated—especially in 2006.

So what are the takeaways? Clearly, there has been a shift in conventional mortgage originations towards borrowers with better credit records. Also, we have to be careful in interpreting the trend in LTV ratios when information on second and third liens is not available. Finally, while survey-based and index measures of availability of credit may be improving, evidence from borrower characteristics of originated mortgages tells a less compelling story and suggests the pendulum still has some distance to go before we can consider it in the loosening range.

Photo of Carl Hudson By Carl Hudson, director for the Center for Real Estate Analytics in the Atlanta Fed´s research department, and

 

Photo of Jessica DillJessica Dill, senior economic research analyst in the Atlanta Fed's research department

March 25, 2015 in Credit conditions | Permalink | Comments (0)

February 25, 2015


Has the Pendulum Swung Back to Neutral? Looking at Credit Availability

Statements since March 2014 from the Federal Open Market Committee, including the last one, indicate that the recovery in the housing sector remains slow. Last year, when the Atlanta Fed looked at measures of housing affordability (see, for example, these posts from the Atlanta Fed blogs macroblog, SouthPoint, and Real Estate Research ), we concluded that in light of the still relatively high readings of affordability measures, it was likely that some other factor was the main culprit in dampening the housing recovery. Access to credit is not included in affordability measures, so in this post, we turn our attention to the question of whether financing might be a headwind to a more robust housing recovery.

The availability of credit is an important driver of housing market activity. During the downturn, our contacts often mentioned that the pendulum had swung too far in the direction of looseness when economic times were good. And during the recovery, they said the pendulum had swung too far in the direction of tightness. In this post, we'll discuss several indicators of credit availability and answer the question, where does the credit availability pendulum hang now?

First, let's look at the Atlanta Fed's monthly poll* of residential brokers and home builders. Beginning with the late 2012 poll, we occasionally included a special question for our panel of real estate business contacts about how available they perceived credit to be. When the Consumer Financial Protection Bureau's (CFPB) Qualified Mortgage (QM) rule went into effect in January 2014, we began asking the credit availability question every month to pick up on subtle changes in perceptions. (The dots on the blue line in chart 1 show the frequency of the question.)

Results from the latest poll suggest that mortgage credit availability is improving. A growing share of business contacts (three-fourths of residential brokers and two-thirds of home builders) reported that the amount of available mortgage finance was sufficient to meet demand. To track the direction of the trend over time, we charted the results in the form of a diffusion index (see the blue line in chart1). A diffusion index value greater than zero signifies that the majority of builders and agents reported that there is enough available credit to meet demand, while a value less than zero signifies that the majority do not believe available credit is sufficient to meet demand. The chart clearly shows that many builders and agents believe there is enough available credit.

Second, let's consider the Mortgage Credit Availability Index (MCAI) that the Mortgage Bankers Association produces on a monthly basis (the green line in chart 1). The MCAI is an index constructed using underwriting criteria from more than 95 lenders and investors. Even though the diffusion index is a qualitative measure and the MCAI is a quantitative measure, the series are highly correlated (ρ=0.73), and both suggest that credit availability has been slowly but steadily improving since early 2013.

Availability-of-credit

Third is the Federal Reserve Board's Senior Loan Officer Opinion Survey on Bank Lending Practices (SLOOS), which polls large domestic and foreign banks every quarter about demand for and the availability of credit. In the SLOOS, banks are asked to indicate whether credit standards for approving mortgage loan applications have tightened, remained unchanged, or eased over the past three months. The latest results, shown in chart 2, reflect recently introduced categories that align with the Consumer Financial Protection Bureau's qualified mortgage rule. Like the previous two series, seen in chart 1, the SLOOS also appears to suggest that lending standards have eased. Note that the net tightening response for prime lending is loosening by a similar or greater magnitude as it did some years during the boom—2006, for example.

Residential-mortgage-lending

So has the credit availability pendulum returned to its neutral resting position? It's hard to say for certain, but there is clearly evidence to suggest that it is at least slowly moving in that direction.

*The monthly poll of brokers and builders was conducted January 12–21, 2015, and reflects conditions in December 2014. Fifty-seven business contacts around the Southeast participated: 23 homebuilders and 34 residential brokers. To explore the latest results in more detail, visit the Construction and Real Estate Survey web page.

Photo of Jessica DillBy Jessica Dill, senior economic research analyst in the Atlanta Fed's research department

February 25, 2015 in Credit conditions, Expansion of mortgage credit, Housing demand | Permalink | Comments (0)

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