-
Yangtze River Delta (29°20′N–32°34′N, 115°46′E–123°25′E) is located on the east coast of China. It includes Shanghai Municipality and Jiangsu, Zhejiang, and Anhui provinces and comprises 26 closely linked cities, with Shanghai as the core. It is the core region of urbanization in China (Fig. 1). The Yangtze River Delta has a developed social economy, a large population and a rapid expansion of construction land, which leads to the problems of disorderly urban space spread, serious construction encroachment on green ecological land, and low degree of conservation and intensive utilization in the process of urban land development. The contradiction between human and land is acute. Therefore, by selecting Yangtze River Delta region as a typical case to explore the impact mechanism of NTU on ULUE, it is more conducive to promoting regional integration and providing reference for the management of urban land intensive use. In 2020, the Yangtze River Delta covered 211 700 km2, with a GDP of 17.86 trillion yuan (RMB) and permanent population of 154 million, accounting for 2.21%, 19.84%, and 11.04% of the national totals, respectively (NBSC, 2020). As a result, there is a growing demand for construction land in the area, which may lead to increasing conflict between regional development and environmental protection.
-
Based on the slack-based measure (SBM) model proposed by Tone (2001), we chose non-radial and non-angle models. The models comprehensively consider the input and output of each decision-making unit (DMU) and put the relaxation variable directly into the objective function, which solves the problem of input-output slacks. Based on this, we developed the SBM-Undesirable model. This model also considers undesirable outputs, making ULUE more accurate in the context of increasing environmental restrictions.
The principle of the model is as follows: there are n homogeneous DMUs, each with three vectors (input, output, and undesirable output), expressed as x, y g and y b, respectively (Liu et al., 2017; Chen et al., 2020). Additionally, X, Y g and Y b are defined as
$X=\left({x}_{i j}\right)$ ,${Y}^{g}=\left({y}_{i j}^{g}\right)$ and${Y}^{b}=\left({y}_{i j}^{b}\right)$ , respectively. Based on the actual input-output, assuming X > 0, Y g > 0 and Y b > 0, the set of production possibilities, that is, all combinations of desirable and undesirable outputs produced by input x of N factors, is P. The model is as follows:$$ \; P = \left\{ {(x,{y^g},{y^b})\left| {x \ge X\lambda ,{y^g} \ge {Y^g}\lambda ,{y^b} \ge {Y^b}\lambda ,\lambda \ge 0} \right.} \right\} $$ (1) According to the definition, the SBM model with undesirable outputs can be defined as:
$$\; {\rho } = \min \left(\frac{{1 - \frac{1}{m}\displaystyle\mathop \sum \limits_{l = 1}^m \frac{{s_l^ - }}{{{x_{l0}}}}}}{{1 + \frac{1}{{{s_1} + {s_2}}}\left(\displaystyle\mathop \sum \limits_{r = 1}^{{s_1}} \frac{{s_r^g}}{{y_{r{0}}^g}} + \displaystyle\mathop \sum \limits_{r = 1}^{{s_2}} \frac{{s_r^b}}{{y_{r{0}}^b}}\right)}} \right)$$ (2) $$ s.t.\left\{ \begin{gathered} {x_{_0}} = X\lambda + {s^ - };\;y_{_0}^g = {Y^g}\lambda - {s^g};\;y_{_0}^b = {Y^b}\lambda + {s^b} \\ {s^ - } \ge 0,\;{s^g} \ge 0,\;{s^b} \ge 0,\lambda \ge 0 \\ \end{gathered} \right. $$ (3) where
$ {s}_{l}^{-} $ is the input slack of lth input variable (l = 1, 2, 3, …, m);$ {s}_{r}^{g} $ and$ {s}_{r}^{b} $ are the desirable and undesirable output slacks, respectively.$x_{l0} $ indicates the investment amount of the r0-th decision-making unit. s1 and s2 represent the number of desirable output variables and undesirable output variables, respectively.${y_{r{0}}^g} $ and${y_{r{0}}^b} $ represent the desirable output and undesirable output of the r0-th decision-making unit, respectively. λ is the weight variable that determines the scale effect of each DMU; and ρ is the comprehensive efficiency of DMU. When ρ = 1, all slacks satisfy$ {s}_{l}^{-}={s}_{r}^{g}={s}_{r}^{b}=0 $ and the kth DMU is efficient. If ρ < 1, DMU is inefficient. The input and output need to be improved. The model is a nonlinear programming model but it can be transformed into a linear programming model using the Charnes-Cooper method (Lu et al., 2018; Yu et al., 2019).To calculate ULUE, the comprehensive benefits to the society, economy, and environment were considered. Additionally, negative environmental effects were included in the index system (Lu et al., 2018; He et al., 2020; Kuang et al., 2020) (Table 1). Following the Cobb-Douglas function, the input indicators used were construction land area, investment in fixed assets, and the number of employees in secondary and tertiary industries. Output indicators were divided into two groups: desirable and undesirable outputs. The desirable output indicators reflected the outcome of the city’s production and operation activities within a certain period. They included economic, social, and environmental benefits, which were the added value of secondary and tertiary industries, average wages of employees, and coverage of green land in built-up areas, respectively. Undesirable output indicators included wastewater discharge, industrial SO2 emissions, and smoke discharge, which were used to characterise the negative environmental effects in the process of urban socio-economic development.
Table 1. Evaluation index used to measure ULUE (urban land use efficiency)
Criterion layer Indicator layer Unit Input Construction land area km2 Investment in fixed assets 100 million yuan (RMB) Number of employees in secondary and tertiary industries 10000 persons Desirable output Added value of secondary and tertiary industries 100 million yuan (RMB) Local general public budget revenue yuan (RMB) Green coverage of built-up area % Undesirable output Wastewater discharge 10000 t Industrial SO2 emissions t Smoke discharge t -
Referencing Peng et al. (2014) and Chen et al. (2016b), the index evaluation system for NTU was defined by four aspects: population, economy, space, and society (Table 2). To avoid the multicollinearity issues caused by the correlation between variables, we used the principal component analysis to calculate the comprehensive result. According to the Kaiser-Meyer-Olkin (KMO) test, the cumulative contribution rate of the first two principal components reaches 90.2%, which meets the general standard wherein the eigenvalue is greater than 1 and the cumulative contribution rate of variance is greater than 85%. Therefore, the selected principal component can represent all the information of the original index. The model is as follows:
Table 2. Indicators used for evaluating the NTU (new-type urbanization) level
Criteria Abbreviation Indicators Unit Population urbanization PU Proportion of urban residents % Proportion of urban employment to total employment % Economic urbanization EU Per capita GDP yuan (RMB) Proportion of the added value of the second and tertiary industry to GDP % Spatial urbanization SU Percentage of built-up area in the total land area % Urban construction land area per capita m2 Social urbanization SCU Average wage of employees yuan (RMB) Proportion of education expenditure to fiscal expenditure % Number of licensed (assistant) doctors per capita person $$ {F _j} = \sum\limits_{u = 1}^n {{L_{u j}}{X_u}} $$ (4) where Fj is the score of principal component j (j = 1, 2), Luj is the loading value of indicator r and principal component j (r = 1, 2, …, 11), and Xu is the normalized evaluation indicator. The comprehensive index was calculated by taking the variance contribution rate of the first two principal components as the weight of each principal component. The specific formula is as follows:
$$ Y = \sum\limits_{j = 1}^m {{W_j}{F _j}} $$ (5) where Y is the NTU index and Wj is the contribution of variance to the principal component j. According to 3σ-principle, the index results can be revised using coordinate transformation.
-
The vector autoregressive (VAR) model, proposed by Sims (1980), was used by He and Peng (2017) to investigate the dynamic impact of external random interference on endogenous variables. However, the VAR model does not support panel data or consider unobservable individual heterogeneity. To overcome these limitations, Holtz-Eakin et al. (1988) extended the VAR model and developed a panel data vector autoregression (PVAR) model. The PVAR has the advantages of both time series and panel data, which is convenient for investigating the dynamic relationship of endogenous variables. The above theoretical framework shows that the relationship between NTU and ULUE is complex and there may be endogenous causality among evaluation units. To determine the influence degree of NTU on ULUE accurately, we established the PVAR model based on the research results of Grossmann et al. (2014) and Kuang et al. (2020). The model can be expressed as:
$$ {y_{it}} = {\alpha _i} + {\beta _0} + \sum\limits_{j = 1}^m {{\beta _j}{y_{i,t - j}}} + {\mu _t} + {\varepsilon _{it}} $$ (6) where i = 1, 2, …, N indicates the evaluation unit, that is, each city in the Yangtze River Delta; t = 1, 2, …, T represents the year; m represents the lag order of the model; yit is the endogenous variable that varies with time and space, including ULUE, PU, EU, SU, and SCU; αi is a vector of fixed effects and stands for the individual differences of the cross section; μt is a vector with time effect; and εit is a random interference term. To avoid heteroscedasticity among variables, all endogenous variables (ULUE, NTU, PU, EU, SU, and SCU) were logarithmically treated and expressed by lnULUE, lnNTU, lnPU, lnEU, LnSU, and lnSCU, respectively.
In addition, Test for stationarity of variables needs to be carried out. The stationarity of panel data is a prerequisite for the PVAR model, which ensures that it has no unit root (Lin and Zhu, 2017). After logarithmic processing of the original data, the unit root test of lnNTU and lnULUE was conducted. There are two types of unit root tests. The first type tests homogeneous unit roots, such as Levine-Lin-Chu (LLC) and Breitung. Another type includes Im, Pesaran and Shin (IPS), Fisher-Augmented Dickey-Fuller (Fisher-ADF), and Fisher-Phillips-Perron (Fisher-PP) tests for homogeneous unit roots. The above five methods were comprehensively adopted to avoid the possible defects of a single test method. The values of lnULUE, lnNTU, lnPU, lnEU, lnSU, and lnSCU were tested. The results in Table 3 show that all variables passed the significance test and have strong stationarity, which can provide a basis for the generalised method of moments (GMM) estimation, impulse response analysis, and prediction variance decomposition.
Table 3. Stationarity test of variables
Statistics Test method LLC Breitung IPS Fisher-ADF Fisher-PP lnULUE –3.2227*** –1.4859* 0.0776 249.0680** 137.6180*** lnNTU –4.6873*** –0.0050 –2.2203** 48.0559* 96.5059*** lnPU –21.7582*** –1.8366** –0.2188 237.2990*** 860.2148*** lnEU –8.0007*** 0.6410 –4.4246*** 65.6057* 1093.8956*** lnSU –4.3290*** –1.4604* –1.3195** 92.4574** 168.0723*** lnSCU –7.5617*** –4.5149*** –10.4704*** 82.8674** 542.1123*** Notes: ***, **, * shows significance at the 1%, 5%, and 10% level, respectively. Urban land use efficiency (ULUE), new-type urbanization (NTU), population urbanization (PU), economic urbanization (EU), spatial urbanization (SU), and social urbanization (SCU). Levine-Lin-Chu (LLC), Im, Pesaran and Shin (IPS), Fisher-Augmented Dickey-Fuller (Fisher-ADF), Fisher-Phillips-Perron (Fisher-PP) -
The data were mainly obtained through public information sources, including China Urban Construction Statistical Yearbook (MHURC, 2000–2020) and China Urban Statistical Yearbook (NBSC, 2000–2020). The indicator of the annual average balance of net fixed assets was converted by consumer price index (CPI) to eliminate the effects of price factor. When processing foreign direct investment data, they were converted into RMB according to the exchange rate of USD/RMB in the current year. The moving average method was used to deal with the missing data of individual years. Based on the above, the city-level data of the Yangtze River Delta from 2000 to 2020 were obtained.
-
The super-efficiency SBM model was used to calculate the land use efficiency of 26 cities in the Yangtze River Delta, with an average value of 1.003 and maximum of 1.063 in 2009 (Fig. 2 and Fig. 3). During the entire study period, ULUE was constantly changing. Especially from 2000 to 2008, ULUE showed a fluctuating upward trend, and the efficiency value increased from 0.987 in 2000 to 1.001 in 2008. The Yangtze River Delta became a key area for attracting foreign investment and developing an export-oriented economy because of its superior geographical location and natural background advantages. The reason might be China’s accession to the World Trade Organisation (WTO) and the accelerated development of economic globalisation. As a result, various development zones with different characteristics, such as high-tech, economic development, and bonded zones, were formed. The total economic volume and development speed accelerated and urban construction land was efficiently utilised. Especially in Jiangsu, the urban land use efficiency (ULUE) increased to 1.034 in 2007, which was more significant than other areas. From 2009 to 2011, ULUE gradually decreased in the Yangtze River Delta; in 2011, it dropped dramatically and the efficiency value was only 0.975. Owing to the adverse effect of global economic crisis in 2008, part of the export-oriented economy of the Yangtze River Delta became unsustainable. Therefore, it is critical to change the mode of economic development and improve the industrial activity in the area. Moreover, under the current strict rules for basic farmland protection, an extensive construction mode for any city (county), development zone, or industrial area is difficult to implement. Urban development has changed from ‘incremental expansion’ to ‘stock tapping’ to improve land use intensity. The land use efficiency of each area decreased in varying degrees and was especially marked in Jiangsu and Anhui. However, some parts of Shanghai and Zhejiang were constrained by the available amount of land, and land use efficiency and development intensity remained at a high level. From 2012 to 2020, global trade protectionism rose and the downward pressure on domestic economic development increased, leading to a growth rate of about 6.0%. The intensity of urban land expansion was not significant and the state had increased its control of land for urban construction. Land use was concentrated around the urban built-up area, mostly to fill spaces in idle suburban land. As a result, ULUE of the Yangtze River Delta changed little and the average efficiency remained at 0.998.
Figure 2. Temporal change of urban land use efficiency (ULUE) in Yangtze River Delta from 2000 to 2020
Figure 3. Temporal change of urban land use efficiency (ULUE) in provinces and municipality of Yangtze River Delta from 2000 to 2020
Data on ULUE in 2000, 2005, 2010, 2015, and 2020 were selected for spatial visualisation (Fig. 4). From the perspective of spatial evolution, ULUE of the Yangtze River Delta varied greatly among different cities and the reasons were complex. From 2000 to 2020, ULUE of Shanghai was much higher than that of other cities, with an average of 1.312. One reason for this is the reuse of inefficient land under government guidance; for example, Shanghai renovated and redeveloped abandoned land in industrial parks to improve ULUE. The second reason is the government’s land-management level; Shanghai adopted an appropriate land use management mode to control disordered expansion to avoid the low efficiency. Nanjing, Hangzhou, Suzhou, and Hefei have high levels of land use efficiency, mainly due to rapid economic development, a strong ability to attract populations from other regions, activation of the amount of land in the built-up area, controlling the amount of new construction land, and improving the intensity of land development investment. All these measures effectively guarantee the rational use of urban land. Correspondingly, the peripheral cities locating in Yangtze River Delta, such as Yancheng, Tongling, Xuancheng, and Jiaxing, need to improve their land use efficiency. There are two reasons for the inefficiency of land use in these cities: first, the policies of sustainable land use in Tongling and Xuancheng are not perfect; second, the expansion mode of urban land ‘from core to edge’ will lead to differences between urban development and land use level, resulting in overall utilisation inefficiency. This situation is particularly prominent in Yancheng City. Since 2000, with the accelerated construction of new urban areas, the extent of the population and industrial suburbanization has been improved. However, land urbanization is proceeding much faster than PU and the ability to attract economic activities and a foreign population is not strong, which makes ULUE remain at a low level.
-
The NTU level in the Yangtze River Delta rose continuously from 2000 to 2020, with an average annual growth rate of 3.47%. From the perspective of the spatial layout (Fig. 5), the spatial differentiation of the NTU level of each evaluation unit was large, showing a certain degree of spatial coupling characteristics with the layout of ULUE. Overall, the ‘core-periphery’ layout features were significant and the high-value areas of the NTU level were distributed along the ‘Huning-Huhang-Hangyong’ traffic trunk line and presented ‘Z’ structure layout characteristics, which were basically consistent with social and economic development levels. Meanwhile, the level of NTU in neighbouring counties was low. The NTU level of the municipality directly under the central government and sub-provincial cities was higher than that of the general prefecture-level cities. This was most obviously true for Shanghai, Nanjing, and Hangzhou. These cities had an efficient administration, a good development foundation, and a low cost of attracting capital, technology, high-end talents, and other advantageous production factors. Therefore, they could take the lead in realizing the requirements of NTU and achieving the goal of sustainable development during social and economic transformation. Correspondingly, Yancheng in the northern Jiangsu, Anqing in the western Anhui, and Jinhua in the northern Zhejiang were the low-level units of NTU. Restricted by the basic geographical conditions of mountains and hills, these areas were mostly designated as ecological conservation areas where industrial development was limited by a severe lack of urban land supply. Despite the constraints of land management policies, the urban extensive growth mode has not been changed, which made the level of NTU low.
-
Before running the PVAR model, this study selected the Akaike Information Criterion (AIC), Bayesian Information Criterion (BIC), and Hannan and Quinn’s Information Criterion (HQIC) to determine the optimal number of lag periods. Decision results of lag period selection were obtained (Table 4). When the lag period was 4, the statistical result of AIC was the lowest. When the lag period was 2, the statistical values of BIC and HQIC were the lowest. Normally, when the results of three criteria were inconsistent, BIC and HQIC were correct. With the gradual increase of the sample size, AIC may mistakenly select an excessively high period, while the independent distribution of BIC and HQIC can select a more accurate lag period. Therefore, the study selected 2 as the lag period.
Table 4. Decision results of lag period selection
Lag Test criteria Conclusion AIC BIC HQIC 1 –14.9778 –13.7359 –14.4883* lag 2 2 –15.7091 –14.2469** –15.1312** 3 –17.0722 –15.6637* –16.6905* 4 –17.3080* –15.3218 –16.5182 Notes: **, * shows significance at the 5%, and 10% level, respectively. Akaike Information Criterion (AIC), Bayesian Information Criterion (BIC), and Hannan and Quinn’s Information Criterion (HQIC) are three test methods for determining lag period Considering the regression variables that may appear in the operation of the model, the forward-mean differencing was used to remove individual effects to realize the orthogonal of the lag variable and transpose variable. Since there may be endogenous problems among variables, the two lag periods of each variable were used as the tool variable and then GMM was used to estimate the PVAR model. In Table 5, when ULUE is an exogenous variable, the first two lag periods have a significant positive effect on the current period, with coefficients of 0.9465 and 0.5345, respectively, indicating that there are positive and progressive effects as well as self-enhancement mechanisms in the time scale of ULUE in Yangtze River Delta. The improvement of ULUE showed a gradual trend and it is necessary to realize intensive and efficient utilisation of urban land through the innovation of land management and utilisation mechanisms. The estimated results are shown in Table 5, where h_lnULUE, h_lnNTU, h_lnPU, h_lnEU, h_lnSU, and h_lnSCU are the sequence of lnULUE, lnPU, lnEU, lnSU, and lnSCU after Helmert transformation; L1 and L2 represent the lag variables of the first cycle and the second cycle, respectively.
Table 5. PVAR (panel vector auto regression) model estimated results by GMM (generalized method of moments) method
Variable Variables Coefficients Standard error Z P h_lnUEUE h_lnULUE L1 0.9465 0.1477 6.41 0.000 h_lnNTU L1 0.3514 0.3516 1.00 0.318 h_lnPU L1 0.1500 0.1187 –1.26 0.206 h_lnEU L1 0.1336 0.1408 –0.95 0.343 h_lnSU L1 –0.0111 0.0078 –1.42 0.154 h_lnSCU L1 –0.1096 0.0901 –1.22 0.224 h_lnULUE L2 0.5345 0.0892 1.51 0.132 h_lnNTU L2 0.2543 0.1722 1.48 0.140 h_lnPU L2 0.1060 0.1377 –0.77 0.442 h_lnEU L2 0.0089 0.0679 –0.13 0.896 h_lnSU L2 –0.0001 0.0089 –0.01 0.989 h_lnSCU L2 –0.0832 0.0507 –1.64 0.101 Notes: L1 and L2 represent lagging periods 1 and 2, respectively. Urban land use efficiency (ULUE), new-type urbanization (NTU), population urbanization (PU), economic urbanization (EU), spatial urbanization (SU), and social urbanization (SCU) During the two lag periods, the NTU level increased by 1% and ULUE increased by 0.3514% and 0.2543%, respectively, indicating that NTU has a promotional effect on ULUE. The reason is that the promotion of NTU, intensive space use, and a compact layout is conducive to the continuous improvement of ULUE. PU and EU had positive effects on ULUE in the two lag periods and both passed the significance test at a 1% level. SU and SCU had negative impacts on ULUE during the two lag cycles but these were not significant. The above results show that the main factors promoting ULUE are population agglomeration and economic growth. In NTU, more attention is paid to the quality of human urbanization and economic development, strictly controlling the disorderly spread of construction land, optimising the land use structure, and promoting the continuous improvement of ULUE.
-
To reveal the dynamic impact trajectory of a random impact with standard deviation, the Monte Carlo method was used to carry out impulse response analysis between NTU and ULUE in the Yangtze River Delta (Fig. 6). The solid red line represents the impulse response value, and the solid blue line represents the estimated values of 5% quantile and 95% quantile, respectively.
Fig. 6a shows that ULUE was impacted by a standard deviation and has a significant positive response to itself. During the first three periods, it had a weak positive U-shape fluctuation. With the extension of time, the continuous positive response had a decreasing trend, which confirms the inertial effect and path dependence characteristics of ULUE in GMM estimation results. However, the cumulative effect intensity decreased continuously. In particular, facing the orthogonalization pulse of lnULUE, the responsivity of lnULUE was 0.1723, which gradually decreased with the increase in the number of subsequent periods. The response degree of lnULUE to itself in stages 5 and 10 was 0.0724 and 0.0162, respectively. Compared with initial stage, they were reduced by 0.0999 and 0.1561. Fig. 6b shows the response of ULUE to a standard deviation of NTU. The results show that ULUE has no apparent response to NTU in the current period. However, it then showed a relatively gentle positive effect trend, presenting an inverted U-shaped feature, which indicates that with the promotion of the NTU policy in the future, the efficient and intensive development of construction land will have a strong pulling effect on ULUE. It peaks in the third year and then the positive response intensity gradually weakens.
Figs. 6c–6f shows the responses of ULUE to the changes in PU, EU, SU, and SCU. There were significant differences in impulse response characteristics. First, the response of ULUE to PU was inconspicuous. In the face of the standard deviation pulse from lnPU, the responsivity of lnULUE in the first period was 0. Then, it dropped to a negative value and moved below 0. After the second period, it gradually rose and converged to 0. The phenomenon indicates that in the process of PU, the production and living of new residents requires a large amount of urban land. Moreover, the expansion of urban land has a negative impact on the improvement of ULUE but the impact is weak. Second, for a standard deviation impulse of lnEU, ULUE did not respond in the current period. From the beginning of the first stage, lnEU showed a positive reaction and the response value increased year by year. In the first period, the response value of lnULUE was 0.0212 peaked. After that, although it decreased year by year, the response remained positive, indicating that the development of EU improves ULUE. Third, the response of lnULUE in the current period was 0 after receiving a standard deviation impulse from the lnSU. After that, the responses of the 5th and 10th periods were –0.0053 and 0.0021, respectively. This indicates that the excessive development of land resources will cause the deterioration of the ecological environment, which is not conducive to the improvement of ULUE. Similar to PU, the impulse response of SCU to ULUE fluctuated during the first four periods. After that, the response tended to be negative but the impact was small. This shows that with the continuous evolution of SCU, the coordination between ULUE and social development will gradually increase.
-
To evaluate the importance of various structural impulses to specific variables, variance decomposition was applied to analyse the importance of different variables to the fluctuation of ULUE. Like the impulse response analysis, the Monte Carlo simulation was carried out 500 times. The results are in Table 6.
Table 6. Variance decomposition results of PVAR model estimated
Variable Lag period / yr Impulse variables lnULUE lnNTU lnPU lnEU lnSU lnSCU lnULUE 1 1.000 0.007 0.010 0.026 0.003 0.001 2 0.985 0.023 0.049 0.039 0.011 0.003 3 0.957 0.050 0.074 0.066 0.020 0.002 4 0.932 0.084 0.113 0.096 0.029 0.002 5 0.909 0.122 0.144 0.125 0.038 0.003 6 0.890 0.159 0.174 0.153 0.046 0.006 7 0.874 0.193 0.199 0.178 0.053 0.011 8 0.861 0.222 0.219 0.200 0.058 0.018 9 0.850 0.247 0.235 0.220 0.063 0.027 10 0.841 0.267 0.249 0.237 0.068 0.039 Notes: Urban land use efficiency (ULUE), new-type urbanization (NTU), population urbanization (PU), economic urbanization (EU), spatial urbanization (SU), and social urbanization (SCU) It can be seen from Table 6 that the first period of lnULUE can explain 100% of its own change, which indicates that the change of ULUE in the Yangtze River Delta is mainly influenced by its own fluctuation. However, the degree of the impact has a downward trend. By the 10th stage, 54.1% of the lnULUE change could be explained by itself. The impulse response of NTU on ULUE was relatively large and showed an increasing trend by year, which means that the impact of NTU on ULUE is a long-term process. From the explanatory power of various types of urbanization on ULUE, the changes in PU, EU, and SU had relatively greater impacts on ULUE, whereas the effect of SCU was smaller. Among them, PU contributed the most to the variation in ULUE, with an average contribution rate of 14.6%. The average contribution rates of EU, SU, and SCU were 13.4%, 3.9%, and 0.11%, respectively. In the first period, lnPU, lnEU, lnSU, and lnSCU had a low degree of explanation for lnULUE, with an average of only 3.8%. However, as time went on, their explanatory power increased and, by the 10th period, their explanatory power on the change of lnULUE was 24.9%, 23.7%, 6.8% and 3.9%, respectively.
Influence Mechanism of New-type Urbanization on Urban Land Use Efficiency in the Yangtze River Delta, China
-
Abstract: Rapid urbanization in China has led to inefficient use of urban land and spatial structure disorder, attracting attention from academia and society. Taking the Yangtze River Delta, China as an example, this study constructed an index evaluation system that quantitatively analyses the impact of new-type urbanization (NTU) on urban land use efficiency (ULUE) from 2000 to 2020 using a panel data vector autoregressive model. The results show that NTU in the Yangtze River Delta promotes ULUE improvement. However, the promotion of NTU to ULUE is limited, and the level of urban economic development also plays a role in promoting the change of ULUE. Moreover, the study further analyzed the results of urbanization decomposition and found that population urbanization (PU), economic urbanization (EU), spatial urbanization (SU), and social urbanization (SCU) can explain changes in ULUE in the Yangtze River Delta to a certain extent. In terms of variance decomposition, PU contributed the most to ULUE, followed by EU, SU, and SCU. Some necessary measures should be taken to coordinate the development of different types of urbanization, improve the sustainable utilization level of land resources, and provide a reference for high-quality development in the Yangtze River Delta.
-
Table 1. Evaluation index used to measure ULUE (urban land use efficiency)
Criterion layer Indicator layer Unit Input Construction land area km2 Investment in fixed assets 100 million yuan (RMB) Number of employees in secondary and tertiary industries 10000 persons Desirable output Added value of secondary and tertiary industries 100 million yuan (RMB) Local general public budget revenue yuan (RMB) Green coverage of built-up area % Undesirable output Wastewater discharge 10000 t Industrial SO2 emissions t Smoke discharge t Table 2. Indicators used for evaluating the NTU (new-type urbanization) level
Criteria Abbreviation Indicators Unit Population urbanization PU Proportion of urban residents % Proportion of urban employment to total employment % Economic urbanization EU Per capita GDP yuan (RMB) Proportion of the added value of the second and tertiary industry to GDP % Spatial urbanization SU Percentage of built-up area in the total land area % Urban construction land area per capita m2 Social urbanization SCU Average wage of employees yuan (RMB) Proportion of education expenditure to fiscal expenditure % Number of licensed (assistant) doctors per capita person Table 3. Stationarity test of variables
Statistics Test method LLC Breitung IPS Fisher-ADF Fisher-PP lnULUE –3.2227*** –1.4859* 0.0776 249.0680** 137.6180*** lnNTU –4.6873*** –0.0050 –2.2203** 48.0559* 96.5059*** lnPU –21.7582*** –1.8366** –0.2188 237.2990*** 860.2148*** lnEU –8.0007*** 0.6410 –4.4246*** 65.6057* 1093.8956*** lnSU –4.3290*** –1.4604* –1.3195** 92.4574** 168.0723*** lnSCU –7.5617*** –4.5149*** –10.4704*** 82.8674** 542.1123*** Notes: ***, **, * shows significance at the 1%, 5%, and 10% level, respectively. Urban land use efficiency (ULUE), new-type urbanization (NTU), population urbanization (PU), economic urbanization (EU), spatial urbanization (SU), and social urbanization (SCU). Levine-Lin-Chu (LLC), Im, Pesaran and Shin (IPS), Fisher-Augmented Dickey-Fuller (Fisher-ADF), Fisher-Phillips-Perron (Fisher-PP) Table 4. Decision results of lag period selection
Lag Test criteria Conclusion AIC BIC HQIC 1 –14.9778 –13.7359 –14.4883* lag 2 2 –15.7091 –14.2469** –15.1312** 3 –17.0722 –15.6637* –16.6905* 4 –17.3080* –15.3218 –16.5182 Notes: **, * shows significance at the 5%, and 10% level, respectively. Akaike Information Criterion (AIC), Bayesian Information Criterion (BIC), and Hannan and Quinn’s Information Criterion (HQIC) are three test methods for determining lag period Table 5. PVAR (panel vector auto regression) model estimated results by GMM (generalized method of moments) method
Variable Variables Coefficients Standard error Z P h_lnUEUE h_lnULUE L1 0.9465 0.1477 6.41 0.000 h_lnNTU L1 0.3514 0.3516 1.00 0.318 h_lnPU L1 0.1500 0.1187 –1.26 0.206 h_lnEU L1 0.1336 0.1408 –0.95 0.343 h_lnSU L1 –0.0111 0.0078 –1.42 0.154 h_lnSCU L1 –0.1096 0.0901 –1.22 0.224 h_lnULUE L2 0.5345 0.0892 1.51 0.132 h_lnNTU L2 0.2543 0.1722 1.48 0.140 h_lnPU L2 0.1060 0.1377 –0.77 0.442 h_lnEU L2 0.0089 0.0679 –0.13 0.896 h_lnSU L2 –0.0001 0.0089 –0.01 0.989 h_lnSCU L2 –0.0832 0.0507 –1.64 0.101 Notes: L1 and L2 represent lagging periods 1 and 2, respectively. Urban land use efficiency (ULUE), new-type urbanization (NTU), population urbanization (PU), economic urbanization (EU), spatial urbanization (SU), and social urbanization (SCU) Table 6. Variance decomposition results of PVAR model estimated
Variable Lag period / yr Impulse variables lnULUE lnNTU lnPU lnEU lnSU lnSCU lnULUE 1 1.000 0.007 0.010 0.026 0.003 0.001 2 0.985 0.023 0.049 0.039 0.011 0.003 3 0.957 0.050 0.074 0.066 0.020 0.002 4 0.932 0.084 0.113 0.096 0.029 0.002 5 0.909 0.122 0.144 0.125 0.038 0.003 6 0.890 0.159 0.174 0.153 0.046 0.006 7 0.874 0.193 0.199 0.178 0.053 0.011 8 0.861 0.222 0.219 0.200 0.058 0.018 9 0.850 0.247 0.235 0.220 0.063 0.027 10 0.841 0.267 0.249 0.237 0.068 0.039 Notes: Urban land use efficiency (ULUE), new-type urbanization (NTU), population urbanization (PU), economic urbanization (EU), spatial urbanization (SU), and social urbanization (SCU) -
[1] Aziz N A, Hassan W H A W, Saud N A, 2012. The effects of urbanization towards social and cultural changes among Malaysian settlers in the Federal Land Development Schemes (FELDA), Johor Darul Takzim. Procedia-Social and Behavioral Sciences, 68: 910–920. doi: 10.1016/j.sbspro.2012.12.276 [2] Bai X M, Shi P J, Liu Y S, 2014. Society: realizing China’s urban dream. Nature, 509(7499): 158–160. doi: 10.1038/509158a [3] Bonafoni S, Baldinelli G, Verducci P, 2017. Sustainable strategies for smart cities: analysis of the town development effect on surface urban heat island through remote sensing methodologies. Sustainable Cities and Society, 29: 211–218. doi: 10.1016/j.scs.2016.11.005 [4] Chen M X, Gong Y H, Lu D D et al., 2019a. Build a people-oriented urbanization: China’s new-type urbanization dream and Anhui model. Land Use Policy, 80: 1–9. doi: 10.1016/j.landusepol.2018.09.031 [5] Chen Mingxing, Ye Chao, Lu Dadao et al., 2019b. Cognition and construction of the theoretical connotation for new-type urbanization with Chinese characteristics. Acta Geographica Sinica, 74(4): 633–647. (in Chinese) [6] Chen Mingxing, Zhou Yuan, Guo Shasha et al., 2019c. Significance, progress and tasks of new-type urbanization research. Advances in Earth Science, 34(9): 974–983. (in Chinese) [7] Chen T T, Hui E C M, Lang W et al., 2016. People, recreational facility and physical activity: new-type urbanization planning for the healthy communities in China. Habitat International, 58: 12–22. doi: 10.1016/j.habitatint.2016.09.001 [8] Chen W, Ning S Y, Chen W J et al., 2020. Spatial-temporal characteristics of industrial land green efficiency in China: evidence from prefecture-level cities. Ecological Indicators, 113: 106256. doi: 10.1016/j.ecolind.2020.106256 [9] Cheshmehzangi A, 2016. China’s new-type urbanisation plan (NUP) and the foreseeing challenges for decarbonization of cities: a review. Energy Procedia, 104: 146–152. doi: 10.1016/j.egypro.2016.12.026 [10] Dadashpoor H, Azizi P, Moghadasi M, 2019. Land use change, urbanization, and change in landscape pattern in a metropolitan area. Science of the Total Environment, 655: 707–719. doi: 10.1016/j.scitotenv.2018.11.267 [11] Deng Wei, Zhang Shaoyao, Zhou Peng et al., 2020. Spatiotemporal characteristics of rural labor migration in China: evidence from the migration stability under new-type urbanization. Chinese Geographical Science, 30(5): 749–764. doi: 10.1007/s11769-020-1147-7 [12] Deng X Z, Gibson J, Wang P, 2017. Relationship between landscape diversity and crop production: a case study in the Hebei Province of China based on multi-source data integration. Journal of Cleaner Production, 142: 985–992. doi: 10.1016/j.jclepro.2016.03.174 [13] Fan Pengfei, Feng Shuyi, Su Min et al., 2018. Differential characteristics and driving factors of land use efficiency in different functional cities based on undesirable outputs. Resources Science, 40(5): 946–957. (in Chinese) [14] Feng W L, Liu Y S, Qu L L, 2019. Effect of land-centered urbanization on rural development: a regional analysis in China. Land Use Policy, 87: 104072. doi: 10.1016/j.landusepol.2019.104072 [15] Grossmann A, Love I, Orlov A G, 2014. The dynamics of exchange rate volatility: a panel VAR approach. Journal of International Financial Markets, Institutions and Money, 33: 1–27. doi: 10.1016/j.intfin.2014.07.008 [16] He C F, Chen T M, Mao X Y et al., 2016a. Economic transition, urbanization and population redistribution in China. Habitat International, 51: 39–47. doi: 10.1016/j.habitatint.2015.10.006 [17] He C F, Zhou Y, Huang Z J, 2016b. Fiscal decentralization, political centralization, and land urbanization in China. Urban Geography, 37(3): 436–457. doi: 10.1080/02723638.2015.1063242 [18] He Haojun, Peng Chong, 2017. The spatial-temporal evolution and the interactive effect between urban industrial structure transformation and land use efficiency. Geographical Research, 36(7): 1271–1282. (in Chinese) [19] He S W, Yu S, Li G D et al., 2020. Exploring the influence of urban form on land-use efficiency from a spatiotemporal heterogeneity perspective: evidence from 336 Chinese cities. Land Use Policy, 95: 104576. doi: 10.1016/j.landusepol.2020.104576 [20] Holtz-Eakin D, Newey W, Rosen H S, 1988. Estimating vector autoregressions with panel data. Econometrica, 56(6): 1371–1395. doi: 10.2307/1913103 [21] Hou Chunguang, Cheng Yu, Ren Jianlan et al., 2016. Spatiotemporal changes and influencing factors of innovation capacity in China. Progress in Geography, 35(10): 1206–1217. (in Chinese) [22] Hu Bixia, Li Jing, Kuang Bing, 2018. Evolution characteristics and influencing factors of urban land use efficiency difference under the concept of green development. Economic Geography, 38(12): 183–189. (in Chinese) [23] Jiao L M, Xu Z B, Xu G et al., 2020. Assessment of urban land use efficiency in China: a perspective of scaling law. Habitat International, 99: 102172. doi: 10.1016/j.habitatint.2020.102172 [24] Koroso N H, Lengoiboni M, Zevenbergen J A, 2021. Urbanization and urban land use efficiency: evidence from regional and Addis Ababa satellite cities, Ethiopia. Habitat International, 117: 102437. doi: 10.1016/j.habitatint.2021.102437 [25] Kuang B, Lu X H, Zhou M et al., 2020. Provincial cultivated land use efficiency in China: empirical analysis based on the SBM-DEA model with carbon emissions considered. Technological Forecasting and Social Change, 151: 119874. doi: 10.1016/j.techfore.2019.119874 [26] Li Zilian, 2013. A study on the causes of population urbanization laging behind land urbanization. China Population Resources and Environment, 23(11): 94–101. (in Chinese) [27] Lin B Q, Zhu J P, 2017. Energy and carbon intensity in China during the urbanization and industrialization process: A panel VAR approach. Journal of Cleaner Production, 168: 780–790. doi: 10.1016/j.jclepro.2017.09.013 [28] Liu H W, Zhang Y, Zhu Q Y et al., 2017. Environmental efficiency of land transportation in China: a parallel slack-based measure for regional and temporal analysis. Journal of Cleaner Production, 142: 867–876. doi: 10.1016/j.jclepro.2016.09.048 [29] Lu X H, Kuang B, Li J, 2018. Regional difference decomposition and policy implications of China’s urban land use efficiency under the environmental restriction. Habitat International, 77: 32–39. doi: 10.1016/j.habitatint.2017.11.016 [30] Ma Haitao, Lu Shuo, Zhang Wenzhong, 2020. Coupling process and mechanism of urbanization and innovation in Beijing-Tianjin-Hebei Urban Agglomeration. Geographical Research, 39(2): 303–318. (in Chinese) [31] Meng F X, Guo J L, Guo Z Q et al., 2021. Urban ecological transition: the practice of ecological civilization construction in China. Science of the Total Environment, 755: 142633. doi: 10.1016/j.scitotenv.2020.142633 [32] MHURC (Ministry of Housing and Urban-Rural Construction of China), 2001–2021. China Urban Construction Statistical Yearbook 2000−2020. Beijing: China Planning Press. (in Chinese) [33] NBSC (National Bureau of Statistics of China), 2001−2021. China City Statistical Yearbook 2000−2020. Beijing: China Statistics Press. (in Chinese) [34] Peng Chong, Chen Leyi, Han Feng, 2014. The analysis of new-type urbanization and the intensive urban land use: spatial-temporal evolution and their relationship. Geographical Research, 33(11): 2005–2020. (in Chinese) [35] Shang Y P, Xu J L, Zhao X, 2022. Urban intensive land use and enterprise emission reduction: new micro-evidence from China towards COP26 targets. Resources Policy, 79: 103158. doi: 10.1016/j.resourpol.2022.103158 [36] Sims C A, 1980. Macroeconomics and reality. Econometrica, 48(1): 1–48. doi: 10.2307/1912017 [37] Sulemana I, Nketiah-Amponsah E, Codjoe E A et al., 2019. Urbanization and income inequality in Sub-Saharan Africa. Sustainable Cities and Society, 48: 101544. doi: 10.1016/j.scs.2019.101544 [38] Sun Pingjun, Lyu Fei, Xiu Chunliang et al., 2015. Basic cognition and evaluation of urban economical and intensive land use under the new urbanization. Economic Geography, 35(8): 178–183,195. (in Chinese) [39] Tone K, 2001. A slacks-based measure of efficiency in data envelopment analysis. European Journal of Operational Research, 130(3): 498–509. doi: 10.1016/S0377-2217(99)00407-5 [40] Wang L, Wong C, Duan X J, 2016. Urban growth and spatial restructuring patterns: the case of Yangtze River Delta Region, China. Environment and Planning B: Urban Analytics and City Science, 43(3): 515–539. doi: 10.1177/0265813515618556 [41] Wu C Y, Wei Y D, Huang X J et al., 2017. Economic transition, spatial development and urban land use efficiency in the Yangtze River Delta, China. Habitat International, 63: 67–78. doi: 10.1016/j.habitatint.2017.03.012 [42] Wu Y Z, Jiang W D, Luo J J et al., 2019. How can Chinese farmers’ property income be improved? A population-land coupling urbanization mechanism. China & World Economy, 27(2): 107–126. doi: 10.1111/cwe.12277 [43] Wu Yifan, Liu Yansui, Li Yurui, 2018. Spatio-temporal coupling of demographic-landscape urbanization and its driving forces in China. Acta Geographica Sinica, 73(10): 1865–1879. (in Chinese) [44] Xiao Y, Zhong J L, Zhang Q F et al., 2022. Exploring the coupling coordination and key factors between urbanization and land use efficiency in ecologically sensitive areas: a case study of the Loess Plateau, China. Sustainable Cities and Society, 86: 104148. [45] Yang J, Sun J, Ge Q S et al., 2017. Assessing the impacts of urbanization-associated green space on urban land surface temperature: a case study of Dalian, China. Urban Forestry & Urban Greening, 22: 1–10. doi: 10.1016/j.ufug.2017.01.002 [46] Yang Qingke, Wang Lei, Qin Xianhong et al., 2022. Urban land use efficiency and contributing factors in the Yangtze River Delta under increasing environmental restrictions in China. Chinese Geographical Science, 32(5): 883–895. doi: 10.1007/s11769-022-1306-0 [47] Yu J Q, Zhou K L, Yang S L, 2019. Land use efficiency and influencing factors of urban agglomerations in China. Land Use Policy, 88: 104143. doi: 10.1016/j.landusepol.2019.104143 [48] Yue Li, Xue Dan, 2020. Study on the impact of new-type urbanization on urban land use efficiency in China. Inquiry into Economic Issues, (9): 110–120. (in Chinese) [49] Zhang Dongling, Wang Yanxia, Liu Min, 2022. The policy-driven effect of new urbanization on the efficiency of green use of urban land: based on the empirical test of 280 prefecture-level. Urban Problems, (4): 45–54. (in Chinese) [50] Zhao Z, Bai Y P, Wang G F et al., 2018. Land eco-efficiency for new-type urbanization in the Beijing-Tianjin-Hebei Region. Technological Forecasting and Social Change, 137: 19–26. doi: 10.1016/j.techfore.2018.09.031 [51] Zhu C M, Zhang X L, Zhou M M et al., 2020. Impacts of urbanization and landscape pattern on habitat quality using OLS and GWR models in Hangzhou, China. Ecological Indicators, 117: 106654. doi: 10.1016/j.ecolind.2020.106654 [52] Zhu X H, Zhang P F, Wei Y G et al., 2019. Measuring the efficiency and driving factors of urban land use based on the DEA method and the PLS-SEM model: a case study of 35 large and medium-sized cities in China. Sustainable Cities and Society, 50: 101646. doi: 10.1016/j.scs.2019.101646