Abstract
Market liberalization reforms in China have led to greater domestic market integration. However, significant urban-rural price differences suggest that segregation between urban and rural markets persists in China. We study the evolution of price differences between urban and rural areas across 25 Chinese provinces over the period 1985-2020. Firstly, we record a substantial and persistent gap between urban and rural price levels within each province. Secondly, we find that this gap narrowed after China implemented the Price Law, which is suggestive of deeper urban-rural integration associated with policy changes. Additionally, we observe notable differences in urban-rural price gaps between provinces, however, using the log-t test, we find evidence of regional convergence in these price gaps. Finally, we investigate the impact of transport infrastructure development on urban-rural price differences. Using spatial econometric analysis and instrumental regressions, we find that road and railway construction has a significant negative effect on the urban-rural price divide, suggesting that infrastructure development facilitates market integration between urban and rural areas in China.
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Notes
Following Brandt and Holz (2006), we use 1990 as the base-year for pricing the basket due to the limited availability of the price data over time.
The data on CPIs originate from the China Statistical Yearbooks and have been retrieved from CSMAR website at http://us.gtadata.com/SingleTable/DataBaseInfo?nodeid=23.
The Law of One Price states that a good must be sold for the same price in all locations if there are no barriers to trade. It implies that convergence of prices across locations appears due to the existence of arbitrage opportunities. The difference in prices of an identical good between any two locations creates an opportunity for sellers to buy the product in a cheaper location and sell it in a more expensive location. This leads to an increase of the demand for the product in the cheap location and therefore pushes prices up. At the same time, the price of the good in the expensive location tends to fall due to the growing supply. Therefore, prices in two locations converge over time thanks to this process of arbitrage.
We check that the distributions of the price differences for urban and rural area are statistically different using the Kolmogorov-Smirnov test of the equality of distributions. The test shows that the null of equality can be rejected at the 1% level. Moreover, we calculate kurtosis values for the urban and rural price differences as a measure of the peakedness of the distribution. We find that the kurtosis values for the distribution of price difference for urban and rural areas are 5.79 and 3.53, respectively, which supports our finding that urban markets in China are more integrated than rural markets.
For each province i we calculate the average relative cost of living as \(\overline{q}^{k}_{it}=\frac{1}{25}\sum _{j=1}^{25} q^{k}_{ijt}\).
Though we exclude key municipalities such as Beijing, Tianjin, Shanghai and Chongqing from our sample due to the lack of data for rural area, we still check whether their inclusion in the analysis of the urban price differences will affect our results. We find that all trends remain unchanged after we add key municipalities to the sample, and the magnitude of price differences changes only slightly. The results are available on request.
Before the reform and opening up in 1978, the Chinese government implemented state-fixed prices for goods and services. The process of price liberalization in China began in the late 1970s when the government introduced the dual-track pricing system, allowing the coexistence of state-fixed prices and market-formulated prices (World Bank 1992). However, the most significant step in the liberalization process is associated with the adoption of the Price Law in 1998, which formally ended the dual-track pricing system and established the market as the primary means of setting most prices.
Before applying the log t-test, we remove the business cycle component from our price gap variable, \(q_{it}\), using the Hodrick-Prescott smoothing filter.
This trimming percentage is suggested by Phillips and Sul (2007) for samples smaller than 50 time-series observations.
Detailed description of the basket construction is available in the online Appendix B of Brandt and Holz (2006) at http://carstenholz.people.ust.hk/SpatialDeflators.html
Following Huang et al. (2020), we calculate road construction as the ratio of road mileage in the province to the administrative area of the province.
Before applying this method, we test the assumption of heteroscedasticity using the Breusch-Pagan/Cook-Weisberg heteroscedasticity test. We find that the null hypothesis of homoscedasticity is rejected, and thus we can use the Lewbel estimator in our model.
Before performing the tests, we construct the spatial distance weight matrix using inverse geographical distance calculated from the coordinate variables.
Crucini and Shintani (2008) and Imbs et al. (2005) show that using micro prices with higher comparability across locations resolves estimation biases associated with the use of aggregate price indices, so the authors estimate relatively faster price convergence when using micro prices as compared to the results based on CPI.
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The authors acknowledge financial support from the Natural Science Foundation of China (project code 71950410627). The participants of the workshop on “Developments in the Convergence and Determinants of Growth and Productivity” are also acknowledged for their valuable comments and suggestions that greatly enhanced the manuscript. Finally, the authors thank two anonymous referees for their valuable comments and accurate insights on the paper.
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Appendices
Appendix
Urban-Rural Price Differences
In this appendix, we provide details of how the Eq. (6) presented in the paper to capture urban-rural price difference was derived. The living expenditure basket consists of a set of products (goods and services), and their weights calculated based on the quantities purchased in the base year. For simplicity, we can group all goods included in the basket into two generalized categories - traded products and non-traded products. So the price of the basket in urban and rural area, \(P^U_{it}\) and \(P^R_{it}\), respectively, could be presented as the cost of traded goods and their share as well as the cost of non-traded goods with their share in living expenditures
where \(\alpha ^U_{i}\) and \(\alpha ^R_{i}\) are the shares of non-traded goods in living expenditures in urban and rural areas, respectively, in province i; \(P^U_{TRit}\) (\(P^R_{TRit}\)) and \(P^U_{NTRit}\) (\(P^R_{NTRit}\)) are expenditures on traded and non-traded goods in urban (rural) area, respectively. Using Eqs. (G1) and (G2) and assuming that the structure of living expenditures does not vary across provinces, i.e. \(\alpha ^U_{i}=\alpha ^U\) and \(\alpha ^R_{i}=\alpha ^R\), we can present the urban-rural price differences as
where \(\frac{(1-\alpha ^U)}{(1-\alpha ^R)}\) and \(\frac{\alpha ^U}{\alpha ^R}\) could be understood as relative shares of traded and nontraded goods in the basket, respectively. Since in our data, \(\alpha ^U\) and \(\alpha ^R\) do not change over time and across provinces, we can denote relative shares of traded and non-traded goods as \(\alpha\) and \(\gamma\), respectively. Then, urban-rural price differences (\(q_{it}=P^U_{it}/P^R_{it}\)) can be presented as
where \(p_{TRit}= P^U_{TRit}/P^R_{TRit}\) and \(p_{NTRit}=P^U_{NTRit}/P^R_{NTRit}\) are relative prices of traded and non-traded goods in province i at time t, respectively.
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Glushenkova, M., Shi, Y. Building Bridges or Walls? Understanding Urban-Rural Price Convergence in China. Open Econ Rev (2024). https://doi.org/10.1007/s11079-024-09765-6
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DOI: https://doi.org/10.1007/s11079-024-09765-6