Is Shenzhen Housing Price Bubble that High? A Perspective of Shenzhen Hong Kong Cross-Border Integration

Transcription

1 Is Shenzhen Housing Price Bubble that High? A Perspective of Shenzhen Hong Kong Cross-Border Integration Yu Zhou (correspondence author), Assistant Professor, Peking University HSBC Business School, Shenzhen, Guangdong, China, , yuzhou@phbs.pku.edu.cn, Phone +(86) Hongru Guo, Analyst, Bank of Communication, Shanghai, China, , ghrphilip@gmail.com Abstract: This paper uses monthly data from May 2004 to December 2011, calculates equilibrium housing price predicted by economic fundamentals of Shenzhen and by additional economic fundamentals of Hong Kong under the background of Shenzhen Hong Kong cross-border integration. Equilibrium housing price is then compared against the actual one to test the degree of Shenzhen housing price bubble during the studied period. We find that aided by economic fundamentals of Hong Kong, Shenzhen housing price can be better explained and the gap between the actual and equilibrium housing price can be largely reduced, implying a much smaller degree of Shenzhen housing price bubble. Key Words: Housing Price Bubble, Shenzhen, Cross-Border, Hong Kong 1. Introduction Shenzhen, the only bordering city of Hong Kong, is one of the first-tier destination cities of real estate investment in Mainland China. Hong Kong was returned to China 1

2 by the British government in year 1997, and since then it has been under a special administration arrangement which makes Hong Kong seemed as a different country from China. One piece of evidence is that today Mainland China citizens still need visa in order for entering Hong Kong. Different administrative system, however, will not cut off cross-border integration, especially from the economic and social perspectives. During recent years, with continuously deepening Shenzhen-Hong Kong integration, a large number of Hong Kong residents get married, secure employment, and or open business in Shenzhen, all of which induce or are induced by local real estate demand. Real estate demand from the other side of the border is further reinforced by the fact that there exists huge cross-border housing price gap of several times, and the fact that the trend of RMB appreciation against HKD encourages even more outside investment into Shenzhen, one of the hottest real estate markets in Mainland China. Evidence from recent data released from Shenzhen Bureau of Land and Resources showed that as high as 8% Shenzhen housing stock is consumed by Hong Kong residents. From one hand, such extra real estate demand has been leading to even sharper rise of Shenzhen housing price considering the inelasticity of housing supply in Mainland China s top cities. Shenzhen housing price has witnessed rapid increase since early this century. As seen from Table 1, housing price in almost every China s big cities was at least doubled during our studied period of Among all these top cities, Shenzhen s case is one of the most extreme. Its housing price was over tripled between 2004 and 2011, following only Fuzhou, Beijing and Ningbo, from about 2

3 6,700 RMB to about 21,000 RMB per square meters within only seven years. Table 1: Yearly Housing Selling Price per Square Meter (in RMB) and Accumulated Growth between 2004 and 2011 for the Biggest 36 Cities of China 1 City Growth 2005:2011 NATIONAL % Fuzhou % Beijing % Ningbo % Shenzhen % Hangzhou % Shijiazhuang % Haikou % Changsha % Wuhan % Guiyang % Tianjin % Chengdu % Zhengzhou % Changchun % Chongqing % Guangzhou % Hohhot % Nanjing % Dalian % Taiyuan % Xiamen % Qingdao % Shanghai % Hefei % Urumqi % Nanchang % Xian % Jinan % Harbin % Xining % 1 We exclude Lhasa, Tibet because of data missing. Data comes from National Bureau of Statistics of China. 3

4 Lanzhou % Shenyang % Yinchuan % Kunming % Nanning % From the other hand, however, cross-border city integration is not the same as city integration among neighboring cities within one country. Cross-border city integration, although with geographic proximity, will still expect large segmentation across the borders resulted from different systems of politics, economy, cultures, etc. After all, cross-border cities are under jurisdiction of different countries (regions); we thus should not expect too much effect on local housing market from aboard factors. Following Beijing and Shanghai, Shenzhen is the next most important GDP giant in Mainland China. However, a comparison of Shenzhen s GDP growth (236% from RMB 342 billion in 2004 to RMB 1150 billion in 2011) to Shenzhen s housing price growth within the same period (216%) shows that over 90% of GDP growth comes from housing price inflation based on that fact that housing price is not included in either the CPI or PPI calculation in China 2. Shenzhen local government, real estate industry and academia should be alert to the evolution of housing price bubble which is potentially caused by soaring housing price deviated from its reasonable level. Burst of housing price bubble will trigger a series of fiscal and financial problems and exert long-term negative effect on affected regions economy and social development. Timely preventive measures are thus necessary for ensuring a real estate market s healthy and sustainable development. Under this consideration, it is practically 2 Data comes from National Bureau of Statistics of China. 4

5 important to make sound judgment on the status of Shenzhen housing market. There is, however, almost no published research on Shenzhen housing price bubble, not to mention from such a novel perspective of Shenzhen Hong Kong cross-border integration. Existing literature provides several ways to test real estate price bubble. For example, Li and Qu (2002) used an efficacy coefficient method to test China s housing market in which three variables (money supply, stock price, and land price) are selected as indicators, evaluation to each one of which is then weighted and summed to obtain a comprehensive judgment of housing market status. They found that from 1986 to 1989 China s housing market was continuously at a warning status of serious housing price bubble. Han (2005), based on West (1987) s model specification testing and the principle that reasonable real estate price should be capitalization of housing rent, to investigate whether housing price bubble existed during in Beijing, Shanghai and Shenzhen. They found mixed results. Ye and Wang (2005) used the Ramsey model to derive the equilibrium real estate value as the marginal return to real estate asset under equilibrium, which is determined by interest rate, inflation, and population. They proposed an interval of equilibrium real estate value by applying upper and lower bounds of interest rate, and then checked whether the actual housing price were outside the proposed interval, which is defined as bubble. They found that China s housing market experienced an evolution of negative bubble, no bubble, and then positive bubble during Yang and Liu (2005) added technical advance and capital depreciation to Ye and Wang (2005) s formula, and re-tested China s housing market over an extended period of

6 They found that the market had experienced a cycle from no bubble, negative bubble to positive bubble. Mikhed and Zemcik (2009) applied the unit root and cointegration tests to US metropolitan housing price and rental fee data between 1978 and The failure of a cointegration relationship between housing price and rental fee indicated the existence of housing price bubble from late 1980s to early 1990s in US major cities. Abraham and Hendershott (1996) utilized growth variables of economic fundamentals to explain the equilibrium housing price growth. Their fundamentals included real construction cost, real per-capita income, employment, and real after-tax interest rate. The housing price bubble could be captured inside the deviation of the actual price from its equilibrium one. Other studies applying the same method to measure housing price bubble include McCarthy et al (2004), Hong et al (2005), Zhou (2005), Pu and Chen (2006), Wu and Wang (2006), among others. This paper adopts Abraham and Hendershott (1996) s method to derive the equilibrium housing price growth in Shenzhen, the deviation of the actual price from which is then calculated as input in the measurement of housing price bubble. Abraham and Hendershott (1996) and others estimated equilibrium housing price using only economic fundamentals of the subject region itself. Realizing strong social and economical cross-border integration between Hong Kong and Shenzhen, this work adds Hong Kong economic fundamentals as foreign prompters of Shenzhen local housing demand to help explain the equilibrium housing price in Shenzhen. 6

7 The next section introduces Abraham and Hendershott (1996) s method. Section 3 discusses our variables and data, followed a few tests to variable and model properties in section 4. Section 5 presents the empirical result, and section 6 concludes. 2. Housing price bubble measurement method According to Abraham and Hendershott (1996), the growth of equilibrium housing price is determined by some economic fundamentals growth as follows: hp k t 0 i 1 ix i (1) where hpt is the growth of equilibrium housing price; explanatory vector xi includes the growth of economic fundamentals, such as construction cost, loan interest rate, per capita disposable income, population, etc. The actual housing price growth, however, is additionally determined by uncertain factors such as market expectation. The actual growth consists of two parts: hp hp e (2) t t t Where hp is actual housing price growth; the error part t e t is what beyond economic fundamentals can capture. By expecting housing price to keep inflating, investors ignore real estate s intrinsic consumption and value maintaining functions, while targeting on speculative returns from buying low and selling high. This leads to so called positive-feedback trading whereby investors make the-next-period investment decision based merely on the past price trend. This positive-feedback trading causes further deviation of actual housing price from its equilibrium one, a development 7

8 mechanism of housing price bubble. The error part et can be expressed as: e hp (ln HP ln HP ) (3) t 0 1 t 1 2 t 1 t 1 t Where hpt 1 is actual housing price growth in the previous period; HP and HPt 1 t 1 are previous-period equilibrium and actual housing price levels, respectively. 1 is the bubble growth coefficient while 2 is the bubble reduction coefficient. If 1 is positive, the previous-period actual housing price growth is to some extent maintained into the current period, a positive-feedback trading mechanism. The difference inside the parenthesis is defined as the forecasting error in the previous period, that is, the deviation of the actual housing price level from its fundamental one. If 2 is negative, the previous forecasting error is corrected in current period towards the equilibrium housing price. t is the random error. Combining equations (1)-(3), the actual housing price growth is derived as: hp x p HP HP (4) k t ( 0 0) 1 i i 1 t 1 2(ln t 1 ln t 1) i t Estimation of equation (4), however, needs know HP sequences, which itself depends on the estimation of equation (4). Abraham and Hendershott (1996) provided the following steps to solve this problem: 1) estimate equation (4) without the 2 HPt 1 HPt 1 (ln ln ) term, and obtain coefficients for other terms; 2) apply coefficient estimates from 1) to estimate HP in equation (1); 3) calculate sums of hpt 1 ln HPt 1 ln HPt 2, hpt 2 ln HPt 2 ln HPt 3,, to get: 8

9 t 1 ln HP ln HP hp (5) t 1 0 i 0 i 4) replace hpi with hpi to obtain ln HP, and a time series { ln HP t 1 ln HP }; 5) t 1 t 1 use results in 4) to estimate equation (4) again to obtain updated coefficients; iterate this process until coefficient estimates converge; 6) apply finalized coefficient estimates in 5) to calculate ln HP and t 1 HP ; 7) measure housing price bubble at t 1 time t as ( HP HP ) / HP 100%. t t t 3. Data, variable and model This paper uses monthly data between May 2004 and December 2011, a total of 92 observations. Data sources include National Bureau of Statistics of China, Shenzhen Municipal Bureau of Statistics, China Real Estate Index System, China Economic Information Network Statistics, Hong Kong Census and Statistics Department, Hong Kong Monetary Authority, and Hong Kong Rating and Valuation Department. The dependent variable is Shenzhen housing sale price growth (hp). Explanatory variables include both Shenzhen and Hong Kong fundamentals. The former include Shenzhen housing investment in RMB (Invest), Shenzhen completed housing area (Area), Shenzhen housing construction cost (Cost), Shenzhen sold housing area (Sales), Shenzhen per capita disposable income (Income), Shenzhen interest rate for 5-year-or-longer loans (Rate), and Shenzhen resident population (N). The latter include Hong Kong median income of working population (Income_HK), Hong Kong loan interest rate (Rate_HK), Hong Kong working population (N_HK), and HKD exchange rate against RMB (Exchange). To eliminate inflation effect on housing price, 9

10 all monetary variable and interest rates are deflated by contemporary local CPI. Except for interest rates and exchange rates, variables are calculated as growth to the previous period. Price of houses, like that of any other commodities, is basically determined by supply and demand of houses, and is also affected by price of substitute goods. Here in this research, Invest, Area, Cost and Sales are either local supply variables or local supply affecting variables while Income and N are local demand affecting variables. Local Rate affects both supply and demand of houses in Shenzhen since an increased (decrease) loan rate discourages (encourages) both. The overall effect direction from Rate relies on the mutual contest between supply and demand. Housing located in Shenzhen is a (partial) substitute for Hong Kong housing. Income_HK, N_HK, and Rate_HK are all Hong Kong local housing demand affecting variables. Changed housing demand in Hong Kong is (partially) absorbed by Shenzhen housing market. RMB appreciation (depreciation) against Hong Kong dollar prompts more (fewer) investors to hold more (less) RMB assets including real estates in hot investment destinations of China, like Shenzhen, lifting up (depressing down) local housing price. By observation, our Shenzhen housing investment (Invest) and Shenzhen completed housing area (Area) time series show strong seasonal trends. We applied the X12 procedure provided by Eviews for seasonal adjustment. The raw yearly data of Shenzhen per capita disposable incomes (Income) and Shenzhen resident population (N) are applied the interpolation method to obtain monthly data by assuming 10

11 population and income are growing stably over time. Our dataset has no Hong Kong per capita disposal income information, so we use Hong Kong median income of working population (Income_HK) as proxy. Again we applied the interpolation method to obtain monthly data from its quarterly raw data. Hong Kong releases only yearly resident population, while Hong Kong working population (N_HK) data has a monthly frequency ready for our usage. For a robustness check of this interpolation method, we compared and found high consistence between empirical results using actual monthly N_HK and those using hypothetical monthly Hong Kong working population interpolated from its observed yearly growth 3. As mentioned in the beginning, this paper develops and compares two models: Model I, the equilibrium housing price model based on Shenzhen economic fundamentals versus Model II, the equilibrium housing price model based on both Shenzhen and Hong Kong economic fundamentals, as equation (6) and equation (7) below, respectively. The sign in front of each variable indicates it is growth. The lagged dependent variables on the right hand side of both models are to capture the potential auto regressive property of housing price itself. hp ( ) Invest Area Cost Sales t t 2 t 3 t 4 t Income Rate N hp (ln HP ln HP ) 5 t 6 t 7 t 1 t 1 2 t 1 t 1 t (6) hp ( ) Invest Area Cost Sales t t 2 t 3 t 4 t Income Rate N Income _ HK 5 t 6 t 7 t 8 t Rate _ HK N _ HK Exchange hp _ HK 9 t 10 t 11 t 12 t 1 hp (ln HP ln HP ) 1 t 1 2 t 1 t 1 t (7) 3 Comparison results are available by request. 11

12 4. Test for variables and model properties We applied the ADF stationary test to each time series in equitation (6) and equitation (7). The Schwarz criteria are used to determine the lag order in the ADF tests. ADF test results in Table 2 show all growth or ratio time series used in Model I and Model II are stationary. The existence of heteroscedasticity may cause consequences such as meaningless significance tests for variables, invalid parameter estimations, failure in model prediction, and etc. It is, therefore, advised to carry out a heteroscedasticity test. The null hypothesis is that random disturbances have equal variance in the linear regression (homoscedasticity), and rejection of the null hypothesis indicates existence of heteroscedasticity. We ran the White heteroscedasticity test (excluding White cross terms) for Model I and Model II, respectively. Results in Table 3 and Table 4 show that both models cannot reject the null hypothesis, that is, no heteroscedasticity exists. Table 2: Time Series Stationary Test Results Variables Difference Lag ADF Order Order statistics Prob. hp ΔInvest ΔArea ΔCost ΔSales ΔIncome Rate ΔN ΔIncome_HK Rate_HK ΔN_HK

13 Exchange hp_hk Table 3: Heteroscedasticity Test Results for Model I White Heteroskedasticity Test: F-statistic Probability Obs R-squared Probability Table 4: Heteroscedasticity Test Results for Model II White Heteroskedasticity Test: F-statistic Probability Obs R-squared Probability Next, we carry out autocorrelation tests for residuals, taking 1-10 lag orders. The null hypothesis is that the model has no autocorrelation, and rejection of the null hypothesis indicates existence of autocorrelation. Test results in Table 5 and Table 6 show that in both models, the probabilities are greater than We thus cannot reject the null hypothesis, indicating autocorrelation does not exist in our models. Table 5: Autocorrelation Test Results for Model I Lag Order AC PAC Q-Stat Prob

14 Table 6: Autocorrelation Test Results for Model II Lag Order AC PAC Q-Stat Prob Empirical results The ordinary least squares method is applied to both Model I and Model II. Regression results of Model I based merely on Shenzhen economic fundamentals are shown in Table 7 (statistically insignificant variables are excluded). Adjusted R 2 is 0.70, implying our selected explanatory variables are powerful in explaining variation of Shenzhen housing price growth. The growth of real construction cost (ΔCost) has positive predicting power on housing price growth with a coefficient 0.49, indicating a 1% increase of real construction cost growth leads to a 0.49% increase of housing price growth in Shenzhen. This result is slightly higher than that of Hong et al (2005) using a national sample. Growth of per capita real disposal income (ΔIncome) has significantly positive effect on housing price growth, but effect magnitude is relatively small. The estimated 14

15 coefficient is 0.12, indicating a 1% increase of disposal income growth causes a 0.12% increase of housing price growth in Shenzhen during our studied period. Xiao (2009) found that per capita disposable income does not significantly affect Shanghai housing price, implying Shanghai housing price is not driven mainly by consumption demand but very likely by speculation, a possible reinforcing factor of housing price bubble. The loan interest rate (Rate) negatively affects housing price growth. A 1% increase of interest rate lowers housing price growth by 0.68%, showing the loan interest rate is an important fundamental tool that can help cool down housing price feverish in Shenzhen. Housing supply is relatively inelastic compared to housing demand in China. Increasing loan interest rate thus reduces more demand than supply, leading both housing price and transaction volume to decrease. Iacoviellos (2002) studied housing price determinants in six major European countries (United Kingdom, Germany, France, Italy, Spain, Sweden), and found that over the past 25 years housing prices in all six countries declined whenever interest rate increased. Empirical results from Abraham and Hendershott (1996) also showed a negative relationship between interest rates and property prices. Finally, the population growth (ΔN) has a strong positive relationship with housing price growth, consistent with our expectation and previous literature. 15

16 Table 7: Regression Results of Model I with Shenzhen Fundamentals Only Variables Parameters Estimates t-statistic Constant β 0 +φ ΔCost β ΔIncome β Rate β ΔN β hp t-1 φ (lnhp t-1 - lnhp t-1 ) φ Adjusted R D-W 1.75 F-statistic Prob (F) 0.00,, and denote significant at 1%, 5% and 10% levels, respectively. The φ 1 is positive and significant both statistically and economically, showing that most of the previous period housing price growth is sustained into the current period; a 1% increase in the previous-period drives up current housing price growth by 0.56%. The significantly negative φ 2 (error correction or bubble reduction effect), indicates that once housing price in the previous period deviated from its fundamental one, it is partially corrected towards the fundamental price in the current period. Numerically, if the previous-period actual housing price was 1% higher (lower) than its equilibrium level, current-period housing price growth is reduced (increased) by 0.21%. Smaller magnitude of φ 2, compared to φ 1, indicates a relatively weak self-correcting capability of Shenzhen housing market, a possible channel to form housing price bubble. Implementation of Abraham and Hendershott (1996) method introduced in Session 2 solves out Shenzhen equilibrium housing price sequence HP t, as shown in Figure 1. 16

17 The lower line is the equilibrium housing price calculated, while the upper line is the actual housing price during the period of from May 2004 to December Since year 2004, the actual housing price in Shenzhen has been rising from RMB 8,830 in May 2004 to RMB 21,891 in December 2011 per square meter. The fundamental price is consistently lower than the actually observed market price during that period (positive deviation of market price from its equilibrium), an implication of positive housing price bubble. Figure 2 presents Shenzhen housing price bubble degree from May 2004 to December 2011, calculated as ( HP HP ) / HP 100%. It is observed that the positive housing t t t price bubble keeps increasing rapidly in recent years. The bubble increased from about 20% in 2004 to 55% in 2009, and has been staying at a very high level around 60% since then. 17

18 Figure 1: Actual and Equilibrium Housing Price Based on Shenzhen Fundamentals Only Shenzhen Actual Housing Prices (RMB) Figure 2: Housing Price Bubble Based on Shenzhen Fundamentals Only 2008/ / / / / / / / / /03 Results from Model II with additional Hong Kong explanatory variables are shown in 18

19 Table 8 (insignificant variables are excluded). As convenience of illustration, we also put regression result from Model I in Table 8. Align with Model I, four Shenzhen economic fundamentals (construction cost, income, interest rate, population) still exert the same-direction influence on housing price growth, although effect magnitudes are all slightly shrunk. Adding Hong Kong economic fundamentals increase the model s adjusted R 2 from 0.70 to 0.77, indicative of stronger explanatory power of this augmented model 4. The previous-period Hong Kong housing price growth (hp_hk t-1 ) positively influences Shenzhen current housing price growth. The estimated coefficient, however, is very small being 6%, compared to 54% of the autoregressive effect from hp t-1. Rising Hong Kong housing price reduces local housing demand and the reduced demand is partially satisfied in Shenzhen, which is made possible by cross-border integration of these two cities. 4 Adjusted R 2 does not necessarily increase when adding irrelevant explanatory variables into the model; while R 2 will never decrease when adding more explanatory variables. 19

20 Table 8:Regression Results of Model II with Hong Kong Economic Fundamentals Added Variables Parameters Model II t-statistic Model I Constant Β 0 + φ ΔCost Β ΔIncome Β Rate Β ΔN Β Rate_HK Β Exchange Β hp_hk t-1 Β hp t-1 Φ (lnhp t-1 - lnhp t-1 ) Φ Adjusted R D-W F-statistic Prob (F) ,, and denotes significant at 1%, 5% and 10% levels, respectively. Hong Kong loan interest rate (Rate_HK) negatively affects Shenzhen housing price growth. A 1% decrease would induce a 0.11% increase of Shenzhen housing price growth. As borrowing cost for both housing providers and consumers, interest rate is a common factor that negatively impacts housing supply and housing demand. In the short term if Hong Kong interest rate decreases, Hong Kong house price would increase because demand, being more price elastic, increases more than supply. The increased housing price in Hong Kong would push partial newly created local housing demand out into Shenzhen, lifting up Shenzhen housing price. Compared with the estimated coefficient of Shenzhen loan interest rate (-0.66), Hong Kong interest rate has much smaller effect on Shenzhen housing price. 20

21 Exchange rate (Exchange, HKD against RMB) negatively affects Shenzhen housing price growth. A 1% decrease of exchange rate (RMB appreciation) would increase Shenzhen housing price growth by 0.14%. RMB appreciation prompts more investors to hold more RMB assets including real estates in hot investment destinations of China, like Shenzhen, lifting up local housing price. The Table 9 summaries effects from cross-border variables on Shenzhen housing price growth. Effect magnitudes from Hong Kong interest rate and previous housing price growth are much smaller than those from Shenzhen local interest rate and previous housing price growth, respectively. This indicates Hong Kong and Shenzhen housing markets are still largely segmented in sprite of their gradual integration. Table 9:Effect from Cross-Border Variables on Shenzhen Housing Price Variables Shenzhen Hong Kong Loan Interest Rate Previous Housing Price Growth Exchange Rate The φ 1 in Table 8 shows a bubble reinforcing coefficient of 0.54, indicating a 1% increase of previous period housing price growth would drive up current growth by 0.54%. The bubble reduction coefficient φ 2 is -0.28, indicating that about one fourth of the previous deviation of market price from its equilibrium is corrected in the current period. Compared with effect magnitudes of φ 1 (0.56) and φ 2 (0.23) from 21

22 Model I, φ 1 in Model II decreases to 0.54 while φ 2 increases to This indicates that when Hong Kong economic fundamentals are added to explain Shenzhen housing price, Shenzhen housing market is characterized by weaker bubble reinforcing effect but stronger self-correction capability, which would predict a smaller degree of housing price bubble in Shenzhen. Implementation of Abraham and Hendershott (1996) method re-solves Shenzhen equilibrium housing price HP between May 2004 and December 2011 as shown in Figure 3 where both Shenzhen and Hong Kong fundamentals are considered. Re-calculating housing bubble ( HP HP ) / HP 100% gives Figure 4 below. t t t Figure 3: Actual and Equilibrium Housing Price with Hong Kong Fundamentals Included Shenzhen Actual Housing Prices Shenzhen Equilibrium Housing Prices Decided by Shenzhen Fundamentals Shenzhen Equilibrium Housing Prices Decided by Additional Hong Kong Fundamentals 22

23 Figure 4: Housing Price Bubble with Hong Kong Fundamentals Included Housing Price Bubble Based on Shenzhen Fundamentals Housing Price Bubble Based on Shenzhen and Hong Kong Fundamentals The top line in Figure 3 is Shenzhen actually observed housing price, the middle line is Shenzhen equilibrium housing price predicted by both Shenzhen and Hong Kong fundamentals, and the bottom line is Shenzhen equilibrium housing price predicted by Shenzhen fundamentals only. Comparing the two equilibrium housing price lines in Figure 3, addition of Hong Kong determinants predicts higher levels of Shenzhen equilibrium housing price, reducing the gap between the actual housing price and its equilibrium. The top line in Figure 4 is the bubble measurement using the equilibrium housing price from Model I, while the lower line is the bubble measurement based on the equilibrium housing price from Model II. Figure 4 witnesses larger estimated housing price bubble from Model I than from Model II where both Shenzhen and Hong Kong economic fundamentals are considered explanation factors. Housing 23

24 bubble in Shenzhen measured in Model II has been stabilized at a 30% level since year 2009, compared to the very high level of 60% from Model I. 6. Conclusions This paper finds that equilibrium housing price of Shenzhen can be additionally explained by economic fundamentals from her cross-border city of Hong Kong. Addition of Hong Kong economic fundamentals improves model explanation power, and reduces the gap between the actual and equilibrium housing price of Shenzhen, thus estimating smaller housing price bubble there. Realization of the cross-border effect from Hong Kong fundamentals on Shenzhen housing price can improve our understanding of Shenzhen housing market. There is much work on integrated housing markets from the perspective of city integration within a country, research on cross-country housing market integration, however, is rare. This methodology is also applicable to real estate markets among other actively integrated cross-border cities. Although our work establishes relatively smaller measurement of housing price bubble in Shenzhen, the bubble did accumulate gradually. Local government needs issue creative regulatory policy to cool down the housing price feverish, so as to avoid short term economic disruption and long term serious fiscal and financial crisis in Shenzhen and surrounding regions. 24

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