*Article* **Retirement Age and Housing Consumption: The Case of South Korea**

**Chunil Kim 1, Hyobi Choi <sup>2</sup> and Yeol Choi 3,\***


**Abstract:** South Korea became an aging society in 2000 and will become a super-aged nation in 2026. The extended life expectancy and earlier retirement make workers' preparation for retirement more difficult, and that hardship might lead to poorer living conditions after retirement. As annuity payments are, in general, not enough for retirees to maintain their previous standard of living after retirement, retired households would have to liquidate their financial and real assets to cover household expenditures. As housing takes the biggest share of households' total assets in Korea, it seems to be natural for retirees to downsize their houses. However, there is no consensus in the housing literature on housing downsizing, and the debate is still ongoing. In order to understand whether or not housing downsizing by retirees occurs in Korea, this paper examines the impact of the timing of retirement on housing consumption using an econometric model of housing tenure choice and the consumption for housing. The results show that the early retirement group living in more populated region does not downsize the house, while the timing of retirement is negatively associated with housing consumption for the late retirement group living in the peripheral region.

**Keywords:** retirement; housing downsizing; housing consumption; housing tenure choice

#### **1. Introduction**

Aging is a global issue. According to the definition of the United Nations, when people aged 65 or older account for 7–14 percent of the population, it is called an aging society; when the proportion is between 14 and 20 percent, it is called an aged society; when it is over 20 percent, it is called a super-aged society. For example, Japan, where aging has been taking place more rapidly, became an aging society in 1970, entered an aged society in 1994, and has been a super-aged society since 2005 [1]. South Korea (hereafter, "Korea") is also one of the most rapidly aging countries, with a decreasing birth rate. Korea became an aging society in 2000 and an aged society in August 2017, and will become a super-aged country in 2026.

In 2015, the residual expected life at 65 in Korea was 18.2 years for men and 22.4 years for women. Those numbers have increased over the past 10 years [2]. On the contrary, workers tend to retire earlier prior to the age of 60, even though 60 marks formal retirement. This extended life expectancy and earlier retirement make workers' preparation for retirement more difficult, and that hardship might lead to poorer living conditions after retirement [3,4]. In Korea, only 6.7 percent of retired households have "enough" provisions for living expenses, while 42.2 and 20.9 percent have "insufficient" and "very insufficient" provisions, respectively [5]. In addition, the relative poverty rate for households with household heads aged 66 or older is 53.1 percent. These figures reveal that a significant portion of retired households encounter financial difficulties after retirement. Most retired

**Citation:** Kim, C.; Choi, H.; Choi, Y. Retirement Age and Housing Consumption: The Case of South Korea. *Sustainability* **2021**, *13*, 1286. https://doi.org/10.3390/su13031286

Academic Editors: Grazia Napoli and Pierfrancesco De Paola Received: 30 September 2020 Accepted: 21 January 2021 Published: 26 January 2021

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**Copyright:** © 2021 by the authors. Licensee MDPI, Basel, Switzerland. This article is an open access article distributed under the terms and conditions of the Creative Commons Attribution (CC BY) license (https:// creativecommons.org/licenses/by/ 4.0/).

people rely on annuity income instead of earned income, but annuity payments are generally not high enough to prepare for a satisfactory standard of living after retirement [6–8]. In Korea, 45.3 percent of people aged 55 to 79 received an annuity of KRW (South Korean won) 520,000 (about USD 444 as of 20 September 2020) per month in 2016, and 73 percent received less than 500,000 won [9]. This means that most elderly face difficulties in living a financially stable life. Owing to this insufficient annuity, some retirees who own multi-unit properties let a portion of their residential properties to earn rental incomes [10–12].

There are many people who do not save enough money in preparation for retirement, and they are thus not likely to have the essential financial resources required to maintain their standard of living in retirement [13]. This reality seems to be more significant for the early retirement group. Fisher et al. [14] expected that people who retire early are more likely to spend their wealth compared to individuals who work longer. Retiring early might mean that people have to rely upon their previously accumulated wealth for a longer amount of time.

As houses are the largest assets owned by most households, do retirees downsize their houses? Among these retirees, who downsizes their houses? There is no consensus in the housing literature on housing downsizing, and the debate is still ongoing. On the one hand, retired households downsize their homes for the consumption of non-durable goods after retirement. Those households plan properly for retirement, which supports the life-cycle income hypothesis and the notion of consumption smoothing. According to this premise, in retirement, accumulated assets are decumulated to achieve the desired level of consumption of non-durable goods and services. On the other hand, there is an opposing strand of literature which found a sharp decline in consumption during the early years of retirement. One reason for this "retirement-consumption" puzzle might be the unwillingness or failure to downsize financial and real assets.

This study contributes to the existing literature on the demand for housing by comprehensively considering the simultaneous linkage of housing tenure choice and housing consumption using a rigorous statistical treatment. Specifically, we first calculated the likelihood of owning a house using a logit model. Then, the estimated propensity of home ownership was included in the housing consumption regression equation as an explanatory variable, in order to deal with the simultaneity between housing tenure choice (owning versus renting) and the consumption for housing (dwelling size). We used the 2014 Survey of Household Finances and Living Conditions (SFLC) dataset provided by Statistics Korea. The dataset contains socio-demographic and financial information for households of all generations. We extracted a sample of retired households from the data. Our analysis was divided into four sub-categories by retirement group and region. We posit that retirees show different housing consumption patterns with respect to the timing of retirement. We estimated the housing downsizing equations for the capital region (Seoul, Gyunggi, and Incheon) and for the non-capital region separately, due to the spatial heterogeneity of the housing market in Korea.

This paper is organized as follows. Section 2 discusses the previous literature on retirement and housing. Section 3 describes the data, variables, and research methodology. Section 4 presents the results from housing tenure choice and housing consumption regressions by retirement group and region. In Section 5, we discuss the results of housing downsizing and their implications for the formation of housing policies for older or retired households. Finally, Section 6 provides some brief concluding remarks and the limitations of the research.

#### **2. Related Literature**

#### *2.1. Definition of Retirement*

Studies on retirement have employed different definitions of retirement. It can be defined by whether one participates in an economic activity. If one provides a positive answer to the question "Have you completely stopped working or looking for a job?", one is considered to be a retiree [15]. Another definition is related to a significant change

in working hours or wages. When one's working hours or wages drastically drop below a certain threshold, one is considered to be a retiree [16,17]. This can also be defined by whether one has left one's primary workplace. If a worker has left the workplace in which he or she has worked for the longest period of time, the person is considered to be a retiree, regardless of current job activities [18–21]. Whether or not one receives a retirement annuity can also define the status of retirement. When one receives a public or private annuity, one is a retiree [22]. Finally, retirement is defined by one's subjective assessment. If one provides a positive answer to the question "Are you currently retired?", one is considered to be a retiree [23,24].

The SFLC data used in this study contain the respondents' subjective assessment. Additionally, retirement is formally defined in South Korea as "the state of being retired from one's business or occupation." First, this study defines retirees as those who answered "yes" to the question "Are you currently retired?" in the SFLC. As for the age cut-off, we also included the early retirement group. Korea's effective age of retirement is around 68 for men and 67 for women. These figures are much higher in many other OCED (Organization for Economic Co-operation and Development) nations. Firms, however, tend to be reluctant to employ older workers. Accordingly, many employers in Korea often set the "mandatory retirement" policy, by which they lay off older workers below the age of 60, as low as 55 [25]. In the SFLC, we observed that some retirees listed their retirement ages as being below 60. We chose to include retirees whose retirement age was equal to or greater than 50, following the study by Kim and Son [26]. The formal retirement age in Korea is 60, similar to many countries. Therefore, we define retirees whose retirement age ranges from 50 to 59 as the "early retirement group", and retirees from the age of 60 to 80 as the "late retirement group". We excluded retirement ages of 81 or above from the analysis.

#### *2.2. Literature on Housing and Retirement Timing*

There are a handful of studies in retirement literature that explore the role of housing in retirement timing. Szinovacz et al. [27] studied the effects of wealth and investment on retirement timing, and found that a decrease in home value is positively related to expectations to work after the age of 62, although the effect is modest relative to other determinants, such as debts and the work environment [28,29]. Farnham and Sevak [30] investigated the effect of the change in housing wealth using the Health and Retirement Study (HRS). They found that a 10 percent increase in housing wealth is associated with a decrease in the expected retirement age of between 3.5 and 5 months. Hartig and Fransson [31] assessed the association between housing tenure and early retirement, and found that housing circumstances have an impact on retirement timing. On the other hand, Gorodnichenko et al. [32] found that home values in the United States have nothing to do with retirement timing, while unemployment rate and inflation are important factors. Similarly, Disney et al. [33] found little evidence of any wealth (housing prices or share prices) effects on retirement timing from the British Household Panel Survey.

#### *2.3. Literature on the Consumption for Housing of Retirees*

Home ownership is a major way to accumulate assets for later life in Korea. Some elderly people might earn rental incomes by holding assets other than houses. Kim and Jeon [34] found that this phenomenon is observed above a certain income decile in South Korea. They showed that the probability of owning additional houses for lease income increases when the household head is married and has school-age children. Similarly, Lin et al. [35] suggested that those who have a higher price-to-income ratio can buy housing for investment purposes in Taiwan. Disney et al. [36] found that there is a strong connection between asset evolution and retirement behavior for later cohorts of retirees in Britain.

The biggest portion of the portfolio of retirees comprises housing assets compared to financial assets in many countries [37]. In Latin America, 90 percent of householders aged 64 or older live in their own houses, whereas only 4 percent live in rented housing [38]. In Taiwan, the older the household head is, the more he or she prefers to buy housing [39]. People aged 60 or older in Hong Kong desire to live in their own housing [40]. This preference for housing assets results from the tendency of the middle-aged and elderly to hedge the risk associated with rent changes in the future by possessing their own housing [41]. In addition, those middle- to old-aged people with real estate assets are more financially well off and better prepared for retirement than those without such assets [10,12]. In Japan, the number of aged people who have their own housing is rising because of the government policy to increase housing welfare by promoting the possession of housing in the postwar period [42].

On the other hand, some studies show that retirees switch from owning to renting or downsize their homes, which is in accordance with the life-cycle income hypothesis [43–46]. Chiuri and Jappelli [47] found that home ownership declines after the age of 70 in most countries by using an international cross-sectional dataset. Older Americans adjust their housing size by around 0.7 of a room smaller than their previous residence [48]. Yogo [49] found that the housing portfolio is negatively related to health for retirees and falls significantly as they age. On the contrary, other studies suggest that such downsizing or reduction is not closely related to aging and retirement [17,50–55].

According to the traditional life-cycle model, retired households who want to reduce the consumption of housing services can liquidate their housing assets through housing downsizing. Artle and Varaiya [56] extended the life-cycle hypothesis to housing, assuming that older households would consume their share of housing after retirement, and predicted that homeowners would convert to rent after retirement. In addition, in the study by Jones [57], the possibility of shifting owning to renting displays a negative relationship with the amount of savings, which is interpreted to support the life-cycle hypothesis. Furthermore, he proposed a revised life-cycle hypothesis, which addresses the fact that housing assets can be liquidated after a significant portion of non-housing assets have been consumed.

However, as many older households were observed to behave differently from the prediction of the life-cycle hypothesis, several alternative hypotheses were suggested. For example, it is argued that socio-demographic changes can lead to tenure transition by reducing the preference for home ownership [52]. They found that the more liquid assets elderly households retain, the lower the probability of housing size reduction becomes.

Venti and Wise [58] conducted a regression analysis of the relationship between the characteristics of moving to owning and the value of housing assets. They found that households with a low income and high housing assets reduce housing assets, while those with a high income and low housing assets increase housing assets. This study revised the life-cycle hypothesis, arguing that homeowners are not moving in order to alleviate liquidity constraints. Some Korean studies, however, found that the liquidity of real estate assets of retirees would be of great importance for their retirement preparation [23,59–61].

#### *2.4. Summary*

In summary, the concept of retirement is somewhat ambiguous, and the definition of retirement is context-dependent. The status of retirement can be judged by an abrupt change in the working hours or wages, by a change of a person's prior major workplace, or by whether or not he or she is in receipt of a retirement pension. The retirement literature is not conclusive about the role of housing in the timing of retirement. A decrease in the housing value might accelerate the timing, and that effect would be less significant, relative to other economic conditions, such as unemployment and inflation. Older households might end up with a bigger housing asset or owning a house. In some cases, they eventually downsize their houses. There are, however, other studies that found little evidence on housing downsizing.

#### **3. Research Methodology**

#### *3.1. Data and Variables*

The SFLC is an annual survey that has been jointly conducted by Statistics Korea, the Financial Supervisory Service, and the Bank of Korea since 2012. The purpose of the SFLC is to support policymaking and research on finance and welfare by comprehensively identifying households' standards of living and the factors affecting their size composition and distribution of assets, debt, and income [2]. This study used the SFLC 2014 data because the sampling design was altered from a fixed panel to a rotating panel in 2015. For our data, 8907 of the 10,000 households provided a complete response for the "Welfare" section of the survey in SFLC 2014. Among those 8907 households, 1454 stated that "the household head has retired." After applying our definition of retirement, we obtained 1337 observations as the effective sample for the analysis.

The dataset was further processed in several ways, in accordance with the purpose of the research. The observations, the retirement age of which is less than 50 and greater than 80, were removed. Then, if the household head was not married or divorced, those households were excluded from the study so that only households with the household head being married or widowed were included. This removal was conducted because there are only 13 and 90 cases for unmarried and divorced households in the data, respectively, and the numbers are thus too small to represent those household groups. Furthermore, cases were removed where other household members (except for the household head and his or her partner) were living with the household head. If a retiree is living with other people (such as his or her children or other relatives), the housing consumption for those households should be systematically different, even after controlling for the timing of retirement. As a result of narrowing the scope of household formation, we ended up focusing on households in one of the following two cases: (i) two-person households with one household head with his or her partner, or (ii) one-person households with one widowed household head without any other family member living together with the household head.

The definitions and measurements of the variables used in this study are presented in Table 1. The housing tenure type (*HTENURE*) is a dummy variable, which takes on the value of 1 if a retired household owns a house. The dwelling size per household member (*AREAPM*) represents the consumption for housing. Clark and Deurloo [62] used the housing size per household member to examine the housing over-consumption behavior for retired households. The dwelling size variable was logged to be used in the regression equations. The probability of owning a house (*OWNPROB*) was estimated using demographic and financial variables, and the likelihood variable was then used as an explanatory variable in the housing consumption equation. *AGE* is the age of the household head in years. *AGERE* represents the retirement age of the household head, indicating the timing of retirement. We wanted to observe the relationships between the retirement age variable and the consumption for housing by region and retirement group. *MSTATUS* indicates the marital status of the household head, which takes on a of value of 1 if a retiree is married and lives with his or her partner, and 0 if he or she is widowed and lives alone. Other types of household member formations were not considered in this research. *NETINC* is the net income variable. We calculated it by subtracting the retired household's expenditures from the total income. The expenditures include consumption expenditures (groceries, residence, education, healthcare, transportation, communication, and family events) and non-consumption expenditures (tax and social insurance fees). *NETASSET* is the net asset variable. A retired household's assets consist of financial and real assets. The financial assets include savings and security deposits. The real assets comprise real estates, automobiles, golf and/or resort membership, jewelry, antiques, and artworks.



#### *3.2. Empirical Strategy*

We recognize that choosing whether to own or rent a house involves an endogenous decision-making process with regard to consumption for housing. King [63] constructed an econometric model of the joint tenure and consumption decision, where both discrete (tenure choice) and continuous (the quantity of housing services) variables are considered using cross-section data. Goodman [64] estimated a joint tenure choice-housing demand model. Ahmad [65] utilized a similar approach for the Karachi housing market. Those studies suggest that ignoring the simultaneity can result in biased elasticity estimates in the equation of housing services. Some studies employed Heckit-type models in regard to the remedy for the simultaneity problem. This study utilized a more direct and intuitively appealing approach, suggested by Fan and Yavas [66], which used the method to study the effect of having a mortgage on household expenditure. In order to tackle the endogeneity problem between housing tenure choice and the level of housing consumption, we first estimated the probability of owning using a logit model. Then, the *estimated* probability was entered into the housing consumption regression equation as an explanatory variable. The two-step process is as follows:

$$\begin{array}{c} \text{Prob}(\text{owning}\_{i} = 1 | \mathbf{X}\_{i}) = \text{ow}\hat{\text{in}}\_{\mathcal{S}i} = F(\mathbf{X}\_{i}^{T}\boldsymbol{\gamma})\\ \log(AREAPM) = \beta\_{0} + \beta\_{1}\text{ow}\hat{\text{in}}ing\_{i} + \beta\_{2}AGREE + \beta\_{3}\Omega\_{i} + \varepsilon\_{i}. \end{array} \tag{1}$$

where *owningi* indicates whether or not a retired household owns a house and *Xi* is a vector of independent variables that affect the household's decision on owning a house. These variables include household demographic and financial characteristics (age of household head, age of retirement, marital status, and net asset), the type of house (apartment or not), and the location of a house (capital area or not). *X<sup>T</sup> <sup>i</sup>* is the transpose of the matrix *Xi*, and *γ* is a vector of parameters for *Xi*. *F* is the cumulative distribution of the logistic distribution. <sup>ˆ</sup> *owningi* denotes the estimated probability of home ownership. log(*AREAPM*) indicates the natural log of the level of housing consumption, which is measured as the log of the dwelling size of a house per household size—the number of household members. Ω*<sup>i</sup>* is a vector of explanatory variables that include the same variables as in *Xi*, plus the current net income stream. The two-step procedure enables us to test whether or not the probability of owning is significantly associated with the consumption for housing by checking the significance of *β*1. Concerning the robustness for the housing consumption equation, a propensity score matching (PSM) analysis was conducted (see Appendix A).

We chose not to include current income in the housing ownership equation because many housing economics studies suggest that housing ownership is more likely to be determined by the level of the long-run expected income, rather than the current or transitory income. On the other hand, the consumption for housing services was estimated for both owners and renters. A renter's housing consumption is more likely to be affected by fluctuation of the current income, relative to owners, because owning involves a higher search

cost and pursuing a new house for owning is relatively costly. Therefore, a higher current income does not necessarily ensure a higher level of housing consumption for owners. Changing the level of housing consumption within the rental market, however, is relatively less costly, so the current net income still might be a responsive factor for the change. Consequently, the current net income can plausibly be included in the housing consumption equation, but not in the tenure choice model. If retirees downsize their houses, the retirement age (*AGERE*) should be negatively related to the quantity of housing services.

#### **4. Results**

#### *4.1. Descriptive Analysis*

The descriptive statistics for the discrete and continuous variables are shown in Tables 2–5. After processing the data in line with the purpose of the research, we obtained 780 households for the whole sample. Among them, the number of households who live in the capital region is 229, and it is 551 for the non-capital region. The ownership rate is 74.62 percent for the whole sample. The rate is slightly lower for the capital region (65.07 percent) in comparison with that for the non-capital region (78.58 percent). The result is reasonable because the difference in housing prices between the two regions outweighs the income differential. We cannot calculate the exact ratio of the number of one-person households to the number of households with two or more household members because this study, by design, eliminated the households with three or more family or non-family members. Among households with one or two members, 50.90 percent are one-person households and 49.10 percent are two-person households. As for the type of housing, retired households in the non-capital region are more likely to live in nonapartment houses, such as single, detached houses or town houses. Breaking the whole sample down into retirement groups with respect to the retirement age, the late retirement group shows a higher home ownership rate in comparison with the early retirement group nationwide (75.00 percent versus 73.17 percent, respectively). For both retirement groups, the home ownership rates in the non-capital region are higher than those in the capital region. A similar pattern can be observed for the percentages of one-person households and non-apartment houses: They are higher in the non-capital region for both groups.


**Table 2.** Descriptive statistics for nominal variables (all retirees).


**Table 3.** Descriptive statistics for continuous variables (all retirees).

<sup>1</sup> *AREAPM* indicates the dwelling size per household member (m2).


**Table 4.** Descriptive statistics for continuous variables (early retirement).

<sup>1</sup> *AREAPM* indicates the dwelling size per household member (m2).

Table 3 presents the demographic and financial information for the retired households by region for all retirees. The average age was 54.02 at the time of the survey, and they retired at the age of 64.06 on average. Two important financial variables in investigating the consumption for housing are the current net income (*NETIC*) and the net asset (*NETASSET*). Those variables are measured in KRW 10 million. On average, retired households' yearly net income is KRW 1.7 million. It seems that some households' expenditure exceeds the yearly income (the minimum value of net income is −7.37). According to Kim [67], two out of five elderly households receive financial support from their adult children on a regular basis in Korea. The exact amount of monetary support obtained from their children or other relatives is generally hidden and not fully reported. Taking a close look at the regional difference, retirees living in the non-capital region obtain a higher net income than those living in the capital region on average (mean = 0.21 versus 0.09, respectively). However, the net incomes for the capital region are more dispersed (S.D. = 0.89 versus

0.58, respectively). The average net asset value retained by the capital region's retirees, however, is almost twice as high as the one in the non-capital region (26.01 versus 13.68, respectively). The combination of the relatively lower level of net income with a higher deviation and the higher level of net asset in the capital region might demonstrate that (i) real estate values are higher in the central area and (ii) the income distribution in the capital area is more skewed to the right, relative to the peripheral region. Another explanation for the lower income in the capital region could be that a fraction of retirees with a higher income move to the non-capital region upon retirement. The Korea Research Institute for Human Settlements [68] reported that, from 2005 to 2010, the number of baby boomers in the non-urban areas increased by around 23,000, whereas the number in major urban areas and in the capital region continuously fell. Lim [69] found that older households are more likely to move from capital to non-capital areas.


**Table 5.** Descriptive statistics for continuous variables (late retirement).

<sup>1</sup> *AREAPM* indicates the dwelling size per household member (m2).

Regardless of the location, the early retirement group retains higher levels of financial resources than the late retirement counterpart (Tables 4 and 5). Nationally, the average net income and the net asset for the early retirement group are KRW 2.7 and 184.2 million, respectively. For the early retirement group, those numbers become smaller (1.5 and 170.0 million won, respectively). For the capital region, the net income for the early retirement group is KRW 2.9 million, on average, whereas it is only 0.2 million won for the late retirement group. We suspect that the significant difference between these figures is due to the fact that the older population spend more on medical expenses, and medical treatments in the capital area deliver better services but are much more expensive.

#### *4.2. Housing Tenure Choice of Retirees*

Tables 6–8 exhibit the results from the logistic regressions for housing tenure choice. Table 6 shows the results for all retirees, for retirees living in the capital region, and for retirees living in the non-capital region, without dividing the whole sample into the retirement groups by retirement age. The models for home ownership are further estimated for early and late retirement (Tables 7 and 8). Regarding the result from the whole sample nationwide, the retirement age (*AGERE*), marital status (*MSTATUS*), housing type (*APT*), and regional dummy variable (*CAPITAL*) significantly affect the decision on owning a house. Retirement age is positively related to the probability of owning a house at the alpha level of 0.05. As the positive effect is derived after controlling for the effect of the age of a retiree, we can conclude that retirees who retired later are more likely to own a

house. The positive effect of marital status on home ownership indicates that two-person households are more likely to possess housing property in comparison with one-person households. Net asset is strongly related to the home ownership. Housing type (*APT*) is also strongly associated with the probability of having a home. Retirees in the capital region are more likely to rent a house than those in the non-capital area. The coefficient of *AGERE* is not statistically significant for the capital region. For the non-capital region, this is significant, and the magnitude of the effect is greater than that for the whole sample. For both regions, the coefficients of net asset are positively related to the home ownership probabilities. Housing type is not a determinant for home ownership in the capital region.


**Table 6.** Housing tenure choice (whole retirees).

\* *p* < 0.1, \*\* *p* < 0.05, \*\*\* *p* < 0.01.

**Table 7.** Housing tenure choice (early retirement group).


\*\* *p* < 0.05, \*\*\* *p* < 0.01.

As for the early retirement group nationwide, except for the net asset, demographic and financial characteristics are not significant factors for home ownership (Table 7). The retirement age and marital status variables are statistically significant for the non-capital region. Moreover, the magnitudes of those variables in the non-capital region become greater than those for the whole sample. On the other hand, for the late retirement group, retirement age has a significant impact on home ownership nationwide and in the noncapital region (Table 8).


**Table 8.** Housing tenure choice (late retirement group).

\* *p* < 0.1, \*\* *p* < 0.05, \*\*\* *p* < 0.01.

In logistic regression, an odds ratio indicates the constant effect of the independent of interest on the likelihood of an event occurring. In this study, the regression coefficient for *AGERE* is the estimated increase in the natural logarithm of odds of owning a house per unit increase in the retirement age. Therefore, the exponentiated value of the regression coefficient is the odds ratio related to a one-unit increase in the retirement age. Table 9 presents the odds ratios of housing ownership for retirement age by the retiree group and region. For all retirees nationwide, the odds ratio is 1.033, meaning that one-unit increase in the retirement age contributes to a 3.3 percent increase in the likelihood of home ownership at any value of the retirement age. The odd ratio for the late retirement group is greater than that for all retirees (1.055). As for the spatial differential of the odds ratio for all retirees, the ratio for the non-capital is greater than that for the entire area (1.054 versus 1.033, respectively). Furthermore, the ratio for the late retirement group living in the non-capital region is the highest in magnitude (1.092). In sum, the effect of the increase in the odds of home ownership for the late retirement group in the peripheral area is almost three times as high as that for all retirees for the whole nation (a 9.2 percent increase versus a 3.3 percent increase, respectively).

**Table 9.** Odds ratios of housing ownership for retirement age.


<sup>1</sup> The odds ratios are not reported here because the corresponding coefficients are not statistically significant at the alpha level of 0.05.

Figure 1 depicts the probabilities of owning a house for the values of retirement age by region. Figure 1a is derived from the nationwide sample, and Figure 1b from only the late retirement group. The results suggest that the non-capital retirees show higher probabilities for the same levels of retirement age, regardless of the timing of retirement. In Figure 1a, the probability of home ownership for the retirement age of 50 for the entire nation is 87.9 percent with the rest of the predictors being set to their mean values, whereas the probability for the same level of retirement age for the non-capital region is 95.1 percent, which is 7.2 percent higher than that for the whole country. The probability curves for both regions are slightly concave, so the probability differentials become smaller as the values of the retirement age increase. Interestingly, across the non-capital probability curves in Figure 1a,b, the home ownership probabilities are higher for the entire sample than for the late retirement group, up to the retirement age of around 65. From the age of

65, the probabilities for the late retirement group apparently start to exceed those for the entire sample.

#### *4.3. Housing Consumption of Retirees*

In accordance with the empirical design, the relationships between retirement age and the consumption for housing services were finally tested by retirement group and region, after controlling for each retired household's propensity of home ownership (Tables 10–12). From the Breusch–Pagan tests for heteroskedasticity, we could not reject the null hypothesis that the error terms are homoscedastic for all regressions, so we did not estimate robust standard errors for the predictors. The adjusted R<sup>2</sup> figures range from around 0.45 to 0.51, suggesting that the limited sets of variables in this study were satisfactorily selected, without causing further multicollinearity problems.

**Figure 1.** Predicted probabilities of owning a house for retirement age by region: (**a**) All retirees; (**b**) Late retirement group.


**Table 10.** Housing consumption (whole sample).

\* *p* < 0.1, \*\*\* *p* < 0.01.

**Table 11.** Housing consumption (early retirees).


\* *p* < 0.1, \*\* *p* < 0.05, \*\*\* *p* < 0.01.

All regressions suggest that the likelihood of having a home increases the level of housing consumption. The sample of the late retirement group for the capital region exhibits the highest effect (0.0143), meaning that a 1 percent point increase in the probability of home ownership leads to a 1.44 percent increase in dwelling size (100 × [exp(0.0143) − 1] = 1.44%) for the retirees who retired at the age of 60 or later living in the non-capital region. It is worth noting that none of the *AGE* variables exert significant impacts on the dwelling size across different retiree groups and regions. The marital status (*MSTATUS*) variables are negatively associated with the dwelling size in all regressions. As the dependent variable is the living area per person, retired households with two persons consume less dwelling area per person than those with one-person households. While the coefficients for net asset (*NETASSET*) variables are positive and significant in some subsamples, those for net income turned out to be irrelevant to the variation of housing consumption.



\* *p* < 0.1, \*\* *p* < 0.05, \*\*\* *p* < 0.01.

The retirement age (*AGERE*) variables are negatively associated with the consumption for housing in the following samples: (i) the all-retiree sample for the whole country; (ii) the non-capital region for the entire retirement group; (iii) the late retirement group sample for the whole country; (iv) the late retirement group sample for the non-capital region. Therefore, we can conclude that later retirement results in a higher degree of economizing on housing consumption.

Finally, Table 13 reports the percentage change in the housing consumption of retirees for a one-unit and five-unit increase in the retirement age. For example, the coefficient of the retirement age variable for the entire retirement group for the whole country is −0.0079, so the consumption for housing decreases by about 0.787 percent as the retirement age increases by one year (100 × [exp(−0.0079) − 1] = −0.787%). The effect becomes −3.873 percent when the retirement age increases by five years (100 × [exp(−0.0079 × 5) − 1] = −3.873%. As the retired household's average dwelling size is 54.02 m2 per person for all retirees nationwide (shown in Table 3), the amount of housing consumption per person for this group on average is expected to decrease by 0.43 m2 if retirement occurs one year later, ending up with the dwelling size of 53.6 m2. A five-year delay in retirement is associated with a decrease in housing consumption of 2.1 m2 per person, and the resulting level of housing consumption becomes 51.9 m2 per person.

**Table 13.** Effects of retirement age on housing consumption.


<sup>1</sup> The effects are not reported here because the corresponding coefficients are not statistically significant at the alpha level of 0.05.

The magnitude of the economization of housing consumption for one-unit increase in the retirement age for all retirees is greater for the non-capital area than for the entire nation (0.936 percent versus 0.787 percent in terms of absolute values, respectively). As the effects are broken down into subsamples in regard to the timing of retirement, the late retiree group shows a higher degree of sensitivity of retirement timing to the adjustment for housing consumption for the entire nation (1.143 percent versus 0.787 percent in terms of absolute values, respectively). For the non-capital region, the effect for all retirees is greater than that for the late retirement group (0.936 percent versus 0.926 percent in terms of absolute values, respectively). The early retirement group does not show any impact of retirement timing on housing consumption adjustment. This irrelevance between retirement age and dwelling size also applies to the retired households living in the capital region.

#### **5. Discussion**

#### *5.1. Housing Downsizing and Retirement-Consumption Puzzle*

Downsizing homes is defined as "a residential move to smaller quarters and the necessary reduction of personal possessions" [70]. This study provides cross-section evidence that housing consumption by retired households decreases with the age of retirement, supporting the hypothesis of housing downsizing. However, our analysis, in terms of housing downsizing, shows different results when we segment the analysis by retirement group and region: Retired households in the capital region and in the early retirement group do not show the downsizing pattern. Therefore, our results do not follow the notion by Fisher et al. [14], which suggests that early retirement induces a higher degree of liquidation of housing wealth than late retirement.

Our results are partly in line with the so-called "retirement-consumption puzzle" with respect to housing consumption. According to the life-cycle hypothesis, even though income discontinuously decreases with retirement, consumption should not be significantly different from the pre-retirement level with respect to lifetime utility maximization and the resulting consumption smoothing. However, some studies found that, in the case of retired households, not only the income level, but also the consumption level, decreases compared to that before retirement. This phenomenon has been referred to as the retirementconsumption puzzle because it is not satisfactorily explained by the permanent income hypothesis that forms the theoretical basis in exploring household consumption behavior. There are various opinions on what the cause is, to what extent the decline occurs, or whether the phenomenon is common to all retirement groups or specific to certain groups or consumption items.

The paper by Hamermech [71] is a pioneering study presenting evidence on the relationship between consumption and assets using the US Retirement History Survey (RHS). The study found that the average consumption of households in their early retirement period exceeded their income level by about 14%. Furthermore, it was found that these households increased their net financial wealth by sharply reducing the level of consumption within a short period of time after retirement. This means that, if it is difficult to maintain the level of consumption enjoyed at the beginning of retirement because their assets are insufficient, their real consumption is reduced in order to cover the gap. A study by Bank et al. [72] analyzed income and expenditure patterns before and after retirement by retirement age cohort, using the British Family Expenditure Survey data, to explore whether households are saving enough for retirement. The results show that there was a significant decrease in consumption around the time of retirement, which was different from the consumption smoothing framework. Even after taking into account job-related expenses, changes in consumption that may be related to the risk of death, and other determinants, the consumption decline predicted by the model was about 2 percent, while the actual consumption decline in the retirement period was 3 percent. The authors concluded that this behavior results from the decrease in consumption due to unexpected negative shocks. Bernheim et al. [73] also reported similar results. This study estimated consumption patterns for the Panel Study of Income Dynamics (PSID) for 430 households between 1978 and 1990. The authors found that consumption decreased by 14 percent on average at the time of retirement. They interpreted the rapid decline in consumption at

the time of retirement as an action taken by households after inspecting their retirement preparation status. It could be the case that those households reduce consumption in response to future negative shocks.

The puzzle is pertinent to housing. According to the life-cycle hypothesis suggested by Ando and Modigliani [74], households withdraw accumulated financial and housing assets for consumption after retirement. Therefore, they increase housing assets when they are young, and reduce those assets when they are getting older. However, there are studies that have tried to modify or refute existing predictions by the life-cycle model related to housing when it comes to the changes in residential status of middle-aged households. Although it has been recognized that older households retain large housing assets and their income levels cannot satisfactorily cover household expenditures, alternative hypotheses have suggested that the possibility of downsizing housing is low if demographic shocks, such as death, illness, or divorce, do not occur, or if people want their children to inherit the housing assets. Beblo and Schreiber [75] found that the strict consumption-smoothing hypothesis is violated for the subgroup of non-home owners for German tenants. Even though our study cannot identify the exact reasons, the results suggest that consumption for housing after retirement *discontinuously* declines. In other words, a decline in housing consumption does not occur through the entire time path after retirement in a smooth way: the reduction in housing consumption does not happen in early retirement, but in late retirement.

#### *5.2. Housing Policy Recommendations*

As the retirement of the baby boomers begins, much attention is being paid to the prediction that older households put their homes on the market through downsizing. In Korea, retiring households' income sources are rapidly decreasing, in part due to the immaturity of public and private pension systems. It is argued that housing represents a high proportion of household assets, and there are relatively few liquid assets that can be used for daily consumption [26]. According to the Korea Housing Finance Corporation [76], 30 percent of the elderly, who own their own homes, had accumulated debts of about KRW 44 million; 20% covered their monthly expenditures with public pensions, such as the national pension, and 40.9% answered that their average income is insufficient.

A reverse mortgage system enables the elderly who own a house to receive a stable monthly income through liquidating housing wealth in the form of a pension. In July 2007, the Korea Housing Finance Corporation launched a reverse mortgage program called "Housing Pension" for the purpose of alleviating the problems of public and private pensions, which are thought to be inefficient in coping with the trend of a rapidly aging society. However, the subscription rate is still low. According to the Korea Housing Finance Corporation, as of January 2017, the 10th year since its inception, the number of subscribers is 40,586. This is less than 1% of 4,969,773 people, which is the population of those aged 60 or older, as of the 2015 Population and Housing Census. The reasons for the low rate include house bequest motivation, expectations for house price appreciation, and the low level of receivable income from the program [77].

The poverty rate of the elderly aged 65 or older in Korea is 43.8%, which is more than triple the average of 14.0% in OECD members [78]. South Korea has a high population density around its capital, which causes housing costs to continuously rise around the area. Therefore, it is difficult for retirees who generally have a relatively low income to own a house in the urban area [79,80]. It turns out that the elderly living in the Seoul metropolitan area are more satisfied with reverse mortgages than the elderly living in non-Seoul areas, as they use such mortgages to cover their relatively high living expenses in the highly dense area [77]. It is thus necessary for the reverse mortgage program to be redesigned, to be expanded, or to be made more accessible to those who retire earlier in the capital region because some retired households might over-consume housing involuntarily [62]. Another concern arises: the reverse mortgage program only supports older home owners. As for the renters, we need to devise policy measures to lower the rental costs, such as

the provision of public housing or direct assistance, that are tailored to those who did not accumulate enough housing wealth to prepare for the later stage of life or to those who experience difficulty moving to a smaller housing unit in the rental housing market.

#### **6. Concluding Remarks**

This paper has investigated the impact of the timing of retirement on housing consumption. Incorporating the endogeneity of housing tenure choice, this study found that households whose household heads retire at the age of 60 or later living in the non-capital region exhibit a negative relationship between the age of retirement and the level of housing consumption, which corresponds to housing downsizing. On the other hand, the early retirement group living in the more populated region does not downsize their house. If the differential impacts of the timing of retirement on housing consumption indicate that the elderly who retire early in the capital region have difficulty reducing their dwelling size in a timely manner, housing policies should pay more attention to revising the current reverse mortgage program or assisting renters through a combination of direct support and the supply of affordable housing.

Three limitations should be addressed. First, we only used the SFLC dataset for one year (2014) because Statistics Korea provides the dwelling size variable as discrete, not continuous, starting from the 2015 dataset, for the sake of increasing confidentiality. As a result, we could not obtain a sufficient number of cases, especially for the early retirement group. Second, we could not add the price variable in the housing consumption regression. We need to estimate the user cost of owning, the rent, and the ratio of those two (the relative price). We could not observe both the value and rent for each observation. In addition, in order to estimate those metrics, we need detailed information on the variables for the hedonic pricing model. The data used in this study lack such information. Finally, because of the limited usability of the data, we could not construct the data as a longitudinal dataset, which has advantages over the one-year data in that we could capture the changes in the retirement status from repeated observations and compare them with the changes of housing consumption. However, given some of the difficulties in using the data, our approach and the results shed some light on the impact of the timing of retirement on housing consumption. We look forward to more studies that examine the spatial heterogeneity of the housing downsizing behaviors for different retirement groups and derive relevant housing policy directions.

**Author Contributions:** Conceptualization, C.K., H.C., and Y.C.; methodology, C.K. and Y.C.; software, C.K.; validation, C.K., H.C., and Y.C; formal analysis, C.K.; writing—original draft preparation, C.K. and H.C.; writing—review and editing, C.K., H.C., and Y.C.; visualization, C.K.; supervision, Y.C.; project administration, Y.C.; funding acquisition, H.C. and Y.C. All authors have read and agreed to the published version of the manuscript.

**Funding:** This research was supported by the Basic Science Research Program through the National Research Foundation of Korea, funded by the Ministry of Science and ICT (NRF-2017R1A2B1010994).

**Institutional Review Board Statement:** Not applicable.

**Informed Consent Statement:** Not applicable.

**Data Availability Statement:** The code and output are available in the Stata log file format upon request.

**Conflicts of Interest:** The authors declare no conflict of interest.

#### **Appendix A. Propensity Score Matching**

As a robustness check, we employed the propensity score matching (PSM) method in order to remove the possible systematic difference of dwelling size between owning and renting. The PSM technique matches observations using the predicted probability of owning from the binary logistic regression. Once the probability is calculated for all households, households with owning are matched with those with renting that have the closest probability. Then, regression equations are re-estimated for the matched samples to ensure the elimination of the systematic bias. This study ended up using the "nearest neighborhood matching with a caliper" algorithm, where the caliper size is a quarter of the standard deviation of the estimated propensity scores.

The matching procedure satisfactorily removed the previous imbalances of dwelling size between owning and renting. Most variables exhibited significant reductions in the differences in means (Table A1). The covariates as a whole also became more balanced after the matching (Table A2). After employing PSM, the coefficient of *AGERE* was not statistically significant (Model 1 in Table A3). We suspected that this result is due to the high level of collinearity between *AGE* and *AGERE*. After removing *AGE* from the model, the coefficient of *AGERE* was significant at the level of *α* = 0.1 (*p*-value = 0.050) (Model 2 in Table A3). We did not employ PSM for other subsamples because the numbers of observations are too small to conduct valid PSM procedures.


**Table A1.** Mean differences of dwelling size between owning and renting.

**Table A2.** Mean and median standardized differences for all covariates.


\* if B > 25%, R outside [0.5; 2].

**Table A3.** Regression results for the whole sample after PSM.


\* *p* < 0.1, \*\* *p* < 0.05, \*\*\* *p* < 0.01.

#### **References**

