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Does off-Farm Migration of Female Laborers Inhibit Land Transfer? Evidence from Sichuan Province, China

Does off-Farm Migration of Female Laborers Inhibit Land Transfer? Evidence from Sichuan Province,... land Article Does o -Farm Migration of Female Laborers Inhibit Land Transfer? Evidence from Sichuan Province, China 1 ,y 2 ,y 1 1 1 , 3 , Kai Huang , Xin Deng , Yi Liu , Zhuolin Yong and Dingde Xu * College of Management, Sichuan Agricultural University, Chengdu 611130, China; hk666@stu.sicau.edu.cn (K.H.); lyx1@stu.sicau.edu.cn (Y.L.); zhuolinyong@stu.sicau.edu.cn (Z.Y.) College of Economics, Sichuan Agricultural University, Chengdu 611130, China; dengxin@sicau.edu.cn Sichuan Center for Rural Development Research, College of Management of Sichuan Agricultural University, Chengdu 611130, China * Correspondence: dingdexu@sicau.edu.cn y These authors contributed equally to this work and should be considered co-first authors. Received: 19 November 2019; Accepted: 7 January 2020; Published: 9 January 2020 Abstract: With the feminization of agriculture, the role of women in the rural land transfer market is becoming increasingly important. However, at present, there is little research focusing on the relationship between the o -farm migration of female laborers and land transfer rates. Using data on 1652 agricultural land plots owned by 232 rural households in Sichuan Province in 2014, IV-Probit (The Probit model of tool variable method is added) and IV-Tobit (The Tobit model of tool variable method is added) models were constructed to explore the relationships between o -farm migration and rural household land transfer (whether the rural households have land transfer-in and the area of land transfer-in by rural households) with consideration of gender. The results show that: (1) O -farm labor migration has a negative and significant impact on rural households’ land transfer-in rates. Under the same conditions, the o -farm migration rate increased by 10%, the probability of transfer-in land decreased by 2.6% on average, and the transfer-in area decreased by 2.7 mu on average. (2) The o -farm migration of female laborers inhibited land transfer-in rates. For every 10% increase in female labor migration, the probability of land transfer-in decreased by an average of 2.1%, and the land transfer-in area was reduced by an average of 3 mu (1 mu = 667 m or 0.067 ha). However, the impact of male labor migration on farmers’ land transfer-in is negative and not significant. This study provides a novel, gendered perspective to understand land transfer-in behaviors in hilly areas, which can provide further information on o -farm labor migration and the rational allocation of land resources. Keywords: land transfer; gender perspective; o -farm labor migration; Sichuan Province; China 1. Introduction Land and labor are the core elements of agricultural production. Farm output quotas are fixed on a household basis in the current system of rural land in China, implemented since the 1980s. It has greatly stimulated the productivity of rural households and rapidly developed the rural economy of China [1–7]. However, due to the restriction of the land quality equalization policy applied when land is contracted for production and assigned to households, cultivated land in the vast, hilly areas of China tends to be “small, scattered, and weak” [8]. With the development of the social economy, the small, scattered, and weak land-use problem has become increasingly prominent and has gradually become a major restriction to China’s rural economic development and food security [9–16]. With the continuous industrialization and urbanization of China, the household contract responsibility system, which Land 2020, 9, 14; doi:10.3390/land9010014 www.mdpi.com/journal/land Land 2020, 9, 14 2 of 14 features decentralized management, is increasingly unable to meet the needs of modern agricultural development, which is characterized by “marketization, scale, and informatization” [17]. It is generally believed in academic circles that the moderate scale of land management plays an important role in limiting land fragmentation. In such management, land transfer is an important method of realizing a moderate scale of land management [18–22]. Land transfer has e ects on the moderate scale management of land, raising rural household income, and preventing land abandonment [23]. Since the mid-1980s, Chinese governments at all levels have successively introduced a series of policies to encourage land transfer and promote the integration of rural land resources [24,25]. Although China has successively issued a series of policies to allow the transfer of “land-use rights” with compensation, the land transfer rate in China has not been high until now. For example, China’s land transfer rate was only 2.53% in 1999. Since the beginning of this century, with the implementation of a series of land policies (such as the “separation of three rights”), the size and form of land transfers in China have changed dramatically. The land transfer rate increased from 12% in 2010 to 37% in 2017, an average annual growth of 17.5% [26]. After 30 years of development of China’s land transfer market, although the transfer rate has increased significantly, it is still relatively low compared with those of other developed countries in Europe and North America, and is even lower than that in China in the last century. For example, the land transfer rate in the United States was 43% in 1992. In 1999, the land transfer rate in Uganda was 36% and, in the Philippines, it was 51% [27,28]. Sichuan is a large, mountainous province in China and a major agricultural province, and its land transfer rate has been lower than the national average. In Sichuan Province in 2016, an area of 19.703 million mu of rural land was transferred (1 mu = 667 m or 0.067 ha), accounting for 33.85% of the household contract management size, and less than the national average of 1.25%. The division of labor in rural households, especially o -farm labor migration, is one of the important causes of this low land transfer rate [29–31]. Since China’s reform and opening up, with the gradual elimination of policy barriers and the transformation of the economic structure, many rural laborers have migrated to cities to seek urban o -farm sector employment [32–34]. Since 1984, when China opened the door for rural residents to work in cities, the rural labor force has decreased while urbanization and industrialization have increased [35–40]. In 1978, the number of rural o -farm workers was 32 million. O -farm payrolls have grown faster since the mid-1980s, reaching 103 million in 1992 and 288 million by the end of 2018. In the 40 years from 1978 to 2018, the number of rural o -farm jobs increased by 257 million in absolute terms, an eight-fold increase [41]. This massive migration of the labor force has resulted in a fundamental structural transformation of the relationship between rural people and land. This not only alleviates the contradiction of “more people and less land” in China, but has also led to demands from political and academic circles for the reallocation of land resources [42]. O -farm labor migration has always been considered an important driver of rural households’ land use (including land transfers) [43,44]. However, inconsistent relationships between o -farm labor migrants and land transfer have been reported in the literature. According to the findings from previous studies, the correlation between the two mainly includes the following three aspects: (1) O -farm employment of the labor force promotes the transfer of rural households’ land. For instance, Deng et al. [45] reported an inverted U-shaped relationship between o -farm employment, land transfer behavior and land transfer size, with inflection points of 55.55% and 56.22%, respectively. Xu et al. [46] reported that o -farm employment encourages rural households to transfer out their land, while part-time employment has an inverted U-shaped relationship with land transfer. Yao et al. [47] reported that o -farm employment can promote the development of the farmland transfer market by increasing the farmland inflow of heterogeneous rural households. The higher is the o -farm employment rate of the rural labor force, the higher is the incidence of land transfer. (2) There is no causal relationship between o -farm employment and land transfer and, to some extent, it will inhibit the development of the land transfer market. For example, Chen et al. [48] reported that there is no causal relationship between the proportion of o -farm labor migration and the proportion of land transfer, and the two Land 2020, 9, 14 3 of 14 do not develop in unison. Qian [49] reported that, due to the increasing rate of rural part-time and agricultural feminization, and the increasing proportion of agricultural machinery inputs, o -farm employment does not accelerate the rate of land transfer. Ma et al. [50] reported that, due to the unique social security function of rural land, o -farm labor migrants often do not give up their land-use rights. (3) They both promote and restrict each other. For example, Li et al. [51] argued that, on the one hand, the migration of surplus rural laborers accelerates the speed of land transfer; on the other hand, due to the urban–rural dual structure, especially the household registration system, insucient o -farm labor migrants inhibit the eciency of land transfer. These above studies have laid a solid foundation with which to understand the correlation between o -farm labor migration and land transfer. However, few studies have focused on the impact of female labor migration on land transfer, especially the impact of female labor migration on land transfer-in, based on gender perspectives with land plots as the research scale. The present study analyzed the impact of female labor migration on land transfer from the perspective of behavioral decision-making of land transfer-in. The reasons for this arrangement are: (1) Under the current household contract responsibility system, the behavior decision of land transfer-in determines the realization of the moderate scale of land management. (2) Among the many factors that still a ect the land transfer level in China, the inhibiting e ect of female labor migration on land transfer-in may be important. Since women are expected to earn far less than men in o -farm employment and are easily burdened by housework, as well as the common divisions of labor that males engage in the o -farm sector and females in the farm sector and the traditional concept of “breadwinning men and homemaking women” in Chinese rural households [52–55], there is hysteresis in female o -farm labor migration and the feminization of agricultural production (the o -farm migration of the female labor force is lower than that of the male labor force). In 2001, 82.1% of rural women were engaged in pure agriculture, while on 64.7% of men. In 2017, 65.2% of migrant workers were male, and 34.8% female [56]. 2. Theoretical Analyses The New Economics of Labor Migration (NELM) was proposed by Stark in the 1980s. Its core idea is that rural households will rationally allocate their labor and land resources on the premise of maximizing family benefits and minimizing risks [57]. Based on this, the present study defined a theoretical model of rural households’ agricultural income maximization as: Y = Y1 Y2 (1) Y1 = XA + TS (2) Y2 = (X + DX)A + (T + DT)S (C + R) (3) In the above equations, Y is agricultural income maximization, Y1 is the family income before the transfer-in of rural households’ land, Y2 is the family income after the transfer-in of rural households’ land, X represents the amount of land contracted by rural households before land transfer-in, A represents the output per unit of land, and XA represents the household’s agricultural income. T is household o -farm employment time, S is the household o -farm employment wage rate, and TS is household o -farm income. DX represents the amount of land change after land transfer-in, DT is the change in o -farm employment time after land transfer, C is the cost of a land ( ) transfer transaction, and R is land transfer. The term X + DX A is household farming income after land transfer-in and (T + DT)S is the household o -farm income after the land transfer-in. If Y < 0, the rural households choose to transfer-in the land; if Y  0, the rural households choose not to transfer-in the land. At the 19th national congress of the communist party of China (CPC) in 2017, the “rural revitalization strategy” was established, which proposed to keep the land contract relationship stable Land 2020, 9, 14 4 of 14 and permanent, and extend it for another 30 years after the second round of land contracts expires [58]. China’s household contract responsibility system will remain unchanged in the long run. Due to the hysteresis of rural female labor migration, the proportion of women in agricultural production is gradually increasing and the female rural labor force has become the main component of rural market economic activities [59]. In 2016, 47.5% of China’s female labor force was engaged in agricultural production, and 52.5% were engaged in non-agricultural production. Theoretically, in a relatively closed environment, the development of technology is relatively slow in the short term and changes in capital input are relatively small. In this case, a certain amount of labor force corresponds to a certain size of land management. When the family labor force migrates for o -farm employment, the area of land that the family can manage decreases, which encourages them to transfer-out land that cannot be cultivated. In contrast, a relative surplus of labor will encourage households to transfer-in the land and expand the scale of production. Therefore, the o -farm migration of female rural laborer may a ect land transfer-in rates in the following ways: (1) When female rural laborers migrate o -farm, the family labor force is insucient and the willingness of rural households to transfer-in land is low. Moreover, as female laborers are the “fresh troops” of agricultural production in the context of agricultural feminization, their o -farm migration will inhibit land transfer-in more than that of men. (2) When female laborers choose to stay behind, it is usually because the expected income of agricultural production and the opportunity cost of o -farm employment are relatively high, and the remaining female labor force increases the family labor force, increasing the ability of rural households to engage in agricultural production. Then, there is an incentive to expand the scale of operation and increase agricultural income, thus they are more willing to transfer-in land. Based on the above theoretical analysis, the present study tested the following research hypotheses: Hypothesis 1 (H1). There is a negative impact of o -farm labor migration on land transfer-in (and the area transfer-in). Hypothesis 2 (H2). Female labor migration has more negative e ect on land transfer-in (and the area transfer-in) than male migration. 3. Data and Methods 3.1. Study Areas Sichuan province, an important exporter of labor to the rest of China and a typical agricultural province, is located in the southwest of China [60]. It covers 486,052 km and had a population of 91.13 million in 2017, of which the rural population was 59.97 million, accounting for 65.58%. Its GDP was 36,980 billion yuan, and its total agricultural output was 40.42 billion yuan. Since the mountainous and hilly terrain area of Sichuan province accounts for about 90% of the total area, the land is not conducive to large-scale agricultural operations [61,62]. 3.2. Data Sources The data used in this research mainly came from a household survey conducted in Guang yuan, Zigong, and Shehong districts (counties) of Sichuan Province, China, in April 2014. This survey used questionnaire-based face-to-face interviews of households, involving questions on family structure (labor force, numbers of elderly members and children, and o -farm payrolls), income (agricultural and non-agricultural income, household agricultural assets, total household assets, etc.), and land use (land transfer, land acquisition, land abandonment, and self-cultivated land). In terms of specific sampling methods, this study adopted with equal probability of selection within the stratum to generate samples. First, based on the studies by Cao et al. (2018), Luo et al. (2007), and Rozella et al. (1996) [63–65], with the per capita gross value of industrial output, 183 districts (counties) in Sichuan Province were divided Land 2020, 9, 14 5 of 14 into three groups. Then, one district (county) was randomly selected from each group to obtain three sample districts (counties). Second, by the same method, all the villages and towns in each sample area (county) were randomly divided into two groups. Third, two villages were randomly selected from each sample township according to their level and location of social and economic development. Finally, 20 rural households were selected randomly from each village by using the village roster and a random number table. Through the above process, questionnaires were obtained from 240 households. After logical screening, valid samples were obtained from 232 households, involving 1652 land plots. The e ective recovery rate of questionnaires was up to 97%. 3.3. Methods 3.3.1. Dependent Variable The dependent variable this study focused on was the transfer-in of rural households’ land, which was mainly measured from two aspects: (1) whether rural households have land transfer-in; and (2) the area of land that rural households transfer-in. 3.3.2. Independent Variable O -farm labor migration with consideration of gender was the independent variable studied in the present study. This study did not strictly distinguish between part-time and o -farm employment, but uniformly classified it as o -farm labor migration. This study mainly measured this by the following two aspects: (1) the impact of o -farm migration on land transfer-in; and (2) the impact of o -farm migration on land transfer-in area. Among them, when investigating the impact of o -farm labor migration on land transfer-in, the core independent variable was the household o -farm labor migration rate, which was measured by the proportion of the total number of o -farm employees and part-time employees in the total labor force. When discussing the influence on land transfer-in from the perspective of gender, the labor migration rate of each gender was used as the focus variable, which was specifically measured by the proportion of male and female o -farm employment and prat-time employment in total household labor force. To reduce the impact of missing variables on the research results, Deng et al. Mullan et al. and Xu et al. [47,48,66] were referred. In this study, the characteristics of the head of a household (such as age and educational level of the head of the household), family characteristics (including area of cultivated land per people, numbers of the elderly and children, whether there are farmers whose age is over 64 years old, the non-current assets of a family, agricultural non-current assets, etc.), and land plots features (such as the presence of irrigation, distance from home, massif terrain attributes, etc.) were included, as the control variables in the model [66,67]. 3.3.3. Method Selection Probit and Tobit models were adopted to explore the impact of o -farm labor migration on whether rural households have land transfer-in and the area of land transfer-in, in consideration of gender. R = + Migration + X + " (4) i 0 1 i i i A = + Migration + X + " (5) i 1 i i i where R and A represent the land transfer-in behavior of household i (whether land is transfer-in i i and the area of land transfer-in, respectively). Migration is the core independent variable of this research model (the proportion of rural labor o -farm migration, the proportion of male labor o -farm migration, and the proportion of female labor o -farm migration). The vector X represents the control variable, is a constant term, " is a disturbance term, and and are the coecients to be estimated 0 i 1 i for the related variables. Land 2020, 9, 14 6 of 14 In addition, due to the possible causal relationship between o -farm labor migration and land transfer-in, the core independent variables in this study may be endogenous. To solve the endogeneity problem in o -farm labor migration, this study set the mean ratio of o -farm labor migration to the total labor force in the same village except the survey households as the instrumental variable. That is: IV Migration = (Migration + Migration + ::: + Migration )/(n 1) Then, IV-Probit and IV-Tobit 1 2 n1 models were used to explore the impact of o -farm labor migration on land transfer-in incidence and area, respectively, to ensure robust results. The model formula was as follows: R = + IV Migration + X +  (6) i 0 1 i i i A = + IV Migration + X +  (7) i 0 1 i i i where the definitions of the variables are similar to those in Equations (4) and (5). The modeling process was conducted using the Stata 13.0 software program (StataCorp. LLC, College Station, TX, USA). 4. Results 4.1. Descriptive Statistical Analysis Table 1 shows the descriptive statistics of the variables involved in the models. The land transfer-in probability and scale were relatively small. Among the 232 sampled rural households, only 2% transfer-in the land. The mean area of the 1652 plots of transfer-in land was 0.01 mu. The per capita cultivated size of the land was 0.86 mu and the average distance from the plot to home was 0.61 km. The household heads were mainly middle-aged and elderly, with low levels of education. The average age of the household head was 58.19 years and the average length of education was 5.91 years. The o -farm labor migration rate was 54.52%, of which men comprised 33.25% and women 21.27%. Table 1. The definition and data description of the variables in the model. Variables Definition and Coding Mean SD Transfer-in Whether the rural households have land transfer-in (1 = Yes; 0 = No) 0.02 0.14 Area -in The area of land transfer-in by rural households (mu ) 0.01 0.12 Migration Labor migration/total household labor force (%) 54.52 28.71 Female-migration Female labor migration/total household labor force (%) 21.27 18.99 Male-migration Male labor migration/total household labor force (%) 33.25 20.44 Head age Age of household head (year) 58.19 10.37 Head edu Education level of household head (year) 5.94 3.4 Per size Per capita cultivated size (mu ) 0.86 0.68 Elder Child Numbers of elderly men and children in the family 1.47 1.14 Elder agri Whether there are elderly farmers > 64 years old (1 = Yes; 0 = No) 0.27 0.44 Fixed asset Household fixed assets (10,000 yuan ) 16.14 20.36 Agri asset Household agricultural fixed assets (10,000 yuan ) 0.38 0.68 Irrigation Whether the plot can be irrigated (1 = Yes; 0 = No) 0.46 0.5 Whether the households’ land has been confirmed the right to Right 0.87 0.34 contract (1 = Yes; 0 = No) Distance Distance from the plot to the home (m) 610.52 829.57 Location 1 Whether the plot is located on a plain (1 = Yes; 0 = No) 0.12 0.32 Location 2 Whether the plot is located on a mountain (1 = Yes; 0 = No) 0.82 0.39 Location 3 Whether the plot is located on a hill (1 = Yes; 0 = No) 0.06 0.25 a 2 b Note: 1 mu = 667 m or 0.067 ha; 1 US dollar = 6.119 Yuan in 2014. 4.2. Econometric Model Results 4.2.1. The Impact of O -Farm Labor Migration on Land Transfer-in Table 2 shows the impact of o -farm labor migration on land transfer-in. Among them, Models 1–5 show the results of the Probit regression model of rural household transfer-in incidence. Among them, Land 2020, 9, 14 7 of 14 Models 1 and 2 are the baseline regressions using the Probit model; Model 1 is the Probit regression including only core variables, while Model 2 includes control variables based on Model 1. Models 3–5 used IV-Probit, and Model 5 is the marginal e ect result obtained by the model. Similarly, Models 6–10 are regressions of the land transfer-in area model; Models 6 and 7 are Tobit baseline regressions, while Models 8–10 are the IV-Tobit models that included the instrumental variable. All models were significant at a level of p < 0.05, indicating that at least one independent variable in the model was significantly correlated with the dependent variable (Table 2). At the same time, the endogeneity test statistics of Models 3–6 and 8–10 were significant (p < 0.05), indicating that the core independent variable of the model was endogenous and the method of its use was correct. In terms of the impact of o -farm labor migration on rural households’ land transfer-in decisions, Migration negatively a ected rural households’ land transfer-in (p < 0.01) and the results were robust. All other things being equal, every 10% increase in Migration reduced the land transfer-in incidence by 2.6% on average. Migration was significantly and negatively correlated with the land transfer-in area (p < 0.05). With other conditions held constant, every 10% increase in Migration reduced the average transfer-in area by 2.7 mu. Looking at the impact of the other control variables on transfer-in of rural household land, the impact of Head age on Transfer-in was not significant. Head edu was negatively impacted on Transfer-in (p < 0.10). Per size, Right, and Distance were significantly negatively impacted on Transfer-in and Area-in. Agri assets and Irrigated variables were positively impacted on Transfer-in and Area-in. 4.2.2. The Impact of O -Farm Labor Migration on Land Transfer-in from the Perspective of Gender Table 3 shows the impact of O -farm labor migration on land transfer-in from the perspective of gender. Similar to Models 1–10, Models 11–15 show the results of the Probit regression model of whether rural households transfer-in the land. Models 11 and 12 are the benchmark regressions using the Probit model. Model 11 is the Probit regression model including only the core variables, while Model 12 includes the control variables as well. Models 16–20 show the results of the regressions of the area of transfer-in land; Models 16 and 17 are Tobit benchmark models, while Models 18–20 are IV-Tobit models that include the instrumental variable. All models were significant at p < 0.01, indicating that at least one independent variable in each model was significantly correlated with the dependent variable (Table 3). The endogeneity test statistics of Models 13–16 and 18–20 were also significant at p < 0.01, indicating that the core independent variable of each model was endogenous and the method of using the instrumental variables was correct. In terms of the impact of o -farm labor migration on rural household land transfer-in incidence and area, Female migration negatively a ected Transfer-in and Area-in (p < 0.01) and the results were robust. With other conditions held constant, every 10% increase in Female migration reduced Transfer-in by 2.1% on average and Area-in by 3 mu on average. Male migration was not correlated with Transfer-in. In terms of the impact of other control variables on land transfer-in, the impact of household head characteristics on land transfer-in were not significant. Per size, Fixed asset, Right, Distance and Fixed asset were significantly negatively impacted on Transfer-in and Area-in. Elder Child, Agri assets and Irrigated variables were positively impacted on Transfer-in and Area-in. Land 2020, 9, 14 8 of 14 Table 2. Results of the econometric model of the impact of o -farm labor migration on land transfer-in. Whether the Households Have Land Transfer-in The Area of Households’ Land Transfer-in Variables Model 1 Model 2 Model 3 Model 4 Model 5 Model 6 Model 7 Model 8 Model 9 Model 10 Migration 0.0069 *** 0.0101 *** 0.0141 ** 0.0328 *** 0.0026 ** 0.0130 *** 0.0121 ** 0.0247 ** 0.0487 ** 0.0027 ** (0.0014) (0.0031) (0.0056) (0.0041) (0.0012) (0.0048) (0.0059) (0.0121) (0.0191) (0.0012) Head age 0.4385 ** 0.2488 0.0195 0.5086 * 0.4153 0.0233 * (0.2110) (0.1853) (0.0131) (0.2987) (0.2963) (0.0126) Head age 2 0.0039 ** 0.0023 0.0002 0.0045 * 0.0038 0.0002 * (0.0018) (0.0016) (0.0001) (0.0026) (0.0026) (0.0001) Head edu 0.0722 ** 0.0491 * 0.0039 * 0.0763 * 0.0714 0.0040 * (0.0322) (0.0293) (0.0021) (0.0451) (0.0458) (0.0022) Per size 0.9409 * 0.6195 ** 0.0487 ** 0.9504 ** 0.8741 ** 0.0490 * (0.5024) (0.2929) (0.0245) (0.4614) (0.4135) (0.0265) Elder Child 0.2493 ** 0.2315 ** 0.0182 ** 0.2547 * 0.3325 ** 0.0187 ** (0.1147) (0.0948) (0.0086) (0.1500) (0.1630) (0.0086) Elder agri 0.0905 0.2072 0.0163 0.0038 0.3960 0.0222 (0.3921) (0.2931) (0.0248) (0.4127) (0.4847) (0.0249) Fixed asset 0.0246 * 0.0141 0.0011 * 0.0200 *** 0.0150 * 0.0008 (0.0126) (0.0093) (0.0006) (0.0076) (0.0079) (0.0006) Agri asset 0.4753 *** 0.2611 ** 0.0205 *** 0.4684 *** 0.3506 *** 0.0197 *** (0.1391) (0.1132) (0.0066) (0.1280) (0.1243) (0.0075) Irrigation 0.7780 *** 0.4218 ** 0.0331 *** 0.7973 *** 0.6011 ** 0.0337 *** (0.2683) (0.2117) (0.0120) (0.2627) (0.2495) (0.0130) Right 1.4091 *** 0.9264 *** 0.0728 *** 1.5786 *** 1.4498 *** 0.0813 *** (0.2017) (0.2170) (0.0172) (0.4892) (0.4630) (0.0140) Distance 0.0015 *** 0.0011 *** 0.0001 *** 0.0016 *** 0.0015 *** 0.0001 *** (0.0005) (0.0004) (0.0000) (0.0005) (0.0005) (0.0000) Location2 0.3558 * 0.2616 0.0206 0.4360 * 0.4402 * 0.0247 ** (0.2090) (0.1624) (0.0126) (0.2515) (0.2492) (0.0124) Location3 0.4074 0.2372 0.0186 0.4572 0.3747 0.0210 (0.2741) (0.2445) (0.0175) (0.3175) (0.3575) (0.0187) constant 1.7444 *** 11.0168 * 1.3063 *** 5.0303 3.1859 *** 12.8187 2.5491 ** 8.7084 (0.1020) (6.2265) (0.3999) (5.3869) (0.9033) (8.2971) (1.1107) (8.2222) Instrumental variables No No Yes Yes Yes No No Yes Yes Yes Wald  25.4173 *** 133.7751 *** 6.3579 ** 383.9628 *** 383.9628 *** 4.1382 ** 35.3192 *** 35.3192 *** 1.3043 ** 9.5047 *** 9.5047 *** 0.9126 ** 4.8353 ** 4.8353 ** Endogenous Wald N 1652 1652 1652 1652 1652 1652 1652 1652 1652 1652 Note: All numbers in parentheses are robust standard errors. Statistical significance at the 0.1, 0.05, and 0.01 level is denoted by *, **, and ***, respectively. Land 2020, 9, 14 9 of 14 Table 3. Results of the econometric model of the impact of o -farm labor migration on land transfer-in with consideration of gender. Whether the Households Have Land Transfer-in The Area of Households’ Land Transfer-in Variables Model 11 Model 12 Model 13 Model 14 Model 15 Model 16 Model 17 Model 18 Model 19 Model 20 Female-migration 0.0053 * 0.0019 0.0246 *** 0.0374 *** 0.0021 ** 0.0105 * 0.0068 0.0649 *** 0.0570 *** 0.0030 *** (0.0029) (0.0064) (0.0081) (0.0075) (0.0009) (0.0058) (0.0075) (0.0196) (0.0177) (0.0010) Male-migration 0.0081 *** 0.0165 *** 0.0286 *** 0.0107 0.0006 0.0133 *** 0.0157 *** 0.0744 *** 0.0255 * 0.0014 * (0.0025) (0.0046) (0.0037) (0.0089) (0.0005) (0.0044) (0.0052) (0.0132) (0.0132) (0.0008) Head age 0.4153 ** 0.2400 0.0133 0.4807 ** 0.3545 0.0189 * (0.2086) (0.1908) (0.0093) (0.2372) (0.2343) (0.0112) Head age 2 0.0037 ** 0.0021 0.0001 0.0043 ** 0.0032 0.0002 * (0.0018) (0.0017) (0.0001) (0.0021) (0.0021) (0.0001) Head edu 0.0826 *** 0.0453 0.0025 0.0694 * 0.0464 0.0025 (0.0313) (0.0340) (0.0016) (0.0379) (0.0427) (0.0024) Per size 0.9649 * 0.6868 ** 0.0381 * 0.9143 * 0.8243 * 0.0439 * (0.5355) (0.3031) (0.0212) (0.5040) (0.4485) (0.0242) Elder Child 0.2498 ** 0.2041 * 0.0113 * 0.3059 * 0.3289 ** 0.0175 ** (0.1211) (0.1108) (0.0064) (0.1591) (0.1654) (0.0077) Elder agri 0.1316 0.0479 0.0027 0.0594 0.2343 0.0125 (0.3976) (0.3140) (0.0173) (0.3821) (0.4249) (0.0231) Fixed asset 0.0219 * 0.0139 * 0.0008 * 0.0156 * 0.0119 0.0006 (0.0120) (0.0074) (0.0005) (0.0086) (0.0081) (0.0004) Agri asset 0.5189 *** 0.2835 *** 0.0157 *** 0.4649 *** 0.2910 ** 0.0155 ** (0.1497) (0.0939) (0.0055) (0.1233) (0.1210) (0.0066) Irrigation 0.7681 *** 0.5288 *** 0.0293 *** 0.7861 *** 0.6276 ** 0.0334 *** (0.2658) (0.1848) (0.0112) (0.2820) (0.2672) (0.0116) Right 1.4043 *** 1.1921 *** 0.0661 *** 1.5419 *** 1.5547 *** 0.0828 *** (0.2028) (0.1690) (0.0139) (0.3403) (0.3131) (0.0147) Distance 0.0015 *** 0.0012 *** 0.0001 *** 0.0014 *** 0.0014 *** 0.0001 *** (0.0005) (0.0003) (0.0000) (0.0005) (0.0005) (0.0000) Location2 0.3844 * 0.2630 0.0146 0.2698 0.2316 0.0123 (0.2104) (0.1762) (0.0099) (0.2174) (0.2181) (0.0130) Location3 0.4068 0.3523 0.0195 0.2938 0.3083 0.0164 (0.2716) (0.2384) (0.0130) (0.2638) (0.2926) (0.0156) constant 1.7395 *** 10.2268 * 1.7869 *** 5.5068 3.0188 *** 12.2274 * 4.8842 *** 8.0642 (0.1026) (6.1424) (0.3214) (5.4833) (0.5198) (6.8059) (0.4699) (6.7201) Instrumental variables No No Yes Yes Yes No No Yes Yes Yes Wald  25.4769 *** 147.8286 *** 108.7606 *** 211.5195 *** 211.5195 *** 36.3189 *** 68.1480 *** 68.1480 *** 274.3585 *** 24.8639 *** 24.8639 *** 140.2069 *** 44.3065 *** 44.3065 *** Endogenous Wald N 1652 1652 1652 1652 1652 1652 1652 1652 1652 1652 Note: All numbers in parentheses are robust standard errors. Statistical significance at the 0.1, 0.05, and 0.01 level is denoted by *, **, and ***, respectively. Land 2020, 9, 14 10 of 14 5. Discussion The present study focused on the impact of o -farm labor migration on rural households’ land transfer-in behavior, especially the impact of female labor migration on land transfer-in behavior. Micro survey data of 1652 agricultural plots owned by 232 rural households in hilly areas of Sichuan Province were used under the guidance of NELM theory. IV-Probit and IV-Tobit models were used to analyze the impacts of o -farm labor migration on land transfer-in incidence and area. The contributions of this study are as follows: (1) In exploring the impact of o -farm labor migration on land transfer-in, this study focused on the impact of female o -farm labor migration on land transfer-in. The use of a gender perspective is novel. (2) In exploring the impact of o -farm labor migration on land transfer-in, this study not only examined land transfer-in incidence, but also land transfer-in area, which is more comprehensive and practical. (3) The use of IV-Probit and IV-Tobit models e ectively dealt with the endogeneity problems existing in the models and made their results more accurate. There are some similarities and di erences between this study and previous ones. For example, consistent with [19,29,31,39,67,68] and other studies, o -farm labor migration was negatively correlated with land transfer-in incidence and area. However, unlike the above studies, and especially unlike the conclusion of [31]—that female migration has no significant impact on rural households’ land use—this study analyzed the impact of o -farm labor migration on land transfer from the perspective of gender and concluded that female migration inhibits land transfer-in more than male labor migration does. This may be because under the background of feminization and part-time employment of agriculture, women are the main participants in agricultural production activities and play an increasingly important role in family decision-making. This results in female migration having a greater inhibitory e ect on land transfer-in decision-making than male migration. In addition, the core independent variable setting of this study is di erent from the studies by [8,19,29,46]. This study did not strictly distinguish between part-time and o -farm employment, but classified part-time and o -farm employment as o -farm labor migration. Unlike the studies by [22,45] this study did not further explore whether there was a U-shaped relationship between o -farm migration and land transfer rates. Based on the above discussion and conclusions, we can draw the following policy implications. First, the government should actively complete the confirmation and registration of land ownership as soon as possible, reduce or give up a large number of administrative orders to intervene in land adjustment, keep the first household contract responsibility system unchanged, promote land “separation of three rights” (right to use, right to ownership, and contract right), and stimulate the development of the land transfer market. Second, the government should accelerate the development of rural vocational education and rural professional households and, especially, increase vocational skills training for women remaining in agriculture, to improve the human resources endowment of the female labor force and expand the scale of agricultural production. The government should improve rural social public services and reduce the female’ burden in housework and raising children so that the female labor force can have more energy to participate in rural market activities. Finally, the government should promote rural non-agricultural economic development to promote rural land transfer as well as to improve rural household income structures, increase the agricultural income proportion of household income, especially that of women, raise the economic status and decision-making power of women in the family, and keep the rural labor force in rural development. This study discussed the impact of o -farm migration on land transfer-in by rural households from a gender perspective. This provides a new perspective by which to understand the land transfer-in behaviors of rural households in hilly areas. However, this study has some shortcomings. For example, the influence of o -farm labor migration on land transfer is a dynamic process. This study only analyzed this relationship using cross-sectional data; future studies could use panel data to gain better insights. Additionally, this study only focused on the impact of o -farm migration on land transfer-in, but land transfer has two dimensions: transfer-in and transfer-out. Future studies could also explore the impact of o -farm labor migration on land transfer-out. Moreover, this study adopts the data from Land 2020, 9, 14 11 of 14 the field survey in 2014, which is relatively weak in timeliness. Future studies can be analyzed with the latest data. 6. Conclusions Based on the above analysis, this study drew the following three main conclusions: 1. There was a significant negative impact of o -farm labor migration on the land transfer-in incidence of rural households. Every 10% increase in o -farm labor migration reduced the probability of land transfer-in by 2.6% on average and the area of land transfer-in decreased by 2.7 mu on average. 2. From the perspective of gender, female migration had an obvious inhibitory e ect on land transfer-in. Specifically, for every 10% increase in the female migration rate, the land transfer-in probability decreased by 2.1% on average and the area of land transfer-in decreased by 3 mu on average. At the same time, there was no impact of male migration on rural household land transfer-in rates. 3. Other control variables, such as Head age, Head edu, Right, Per size, Agri asset, and Irrigation, all significantly impact on farmers’ land transfer behavior and area. Author Contributions: Data curation, K.H. and X.D.; Investigation, Y.L. and Z.Y.; Methodology, D.X.; Software, K.H. and Y.L.; Writing—original draft, K.H.; and Writing—review and editing, D.X. All authors have read and agreed to the published version of the manuscript. Funding: This research was funded by National Natural Science Foundation of China (Grant Nos. 41801221, 41571527, 41601614, and 41701622); Innovation training program of Sichuan Agricultural University in 2019 (2019106226105); and Undergraduate research interest cultivation program in 2020 of Sichuan Agricultural University (Study on the relationship between livelihood transformation and sustainable land use of farmers in mountainous areas of Sichuan province). Acknowledgments: We gratefully acknowledge financial supports from National Natural Science Foundation of China (Grant Nos. 41801221, 41571527, 41601614, and 41701622) and Innovation training program of Sichuan Agricultural University in 2019 (2019106226105). The authors also extend great gratitude to the anonymous reviewers and editors for their helpful review and critical comments. Conflicts of Interest: The authors declare no conflict of interest. References 1. De Brauw, A.; Huang, J.; Rozelle, S.; Zhang, L.; Zhang, Y. 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Does off-Farm Migration of Female Laborers Inhibit Land Transfer? Evidence from Sichuan Province, China

Huang, Kai; Deng, Xin; Liu, Yi; Yong, Zhuolin; Xu, Dingde
Land , Volume 9 (1) – Jan 9, 2020
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DOI
10.3390/land9010014
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Abstract

land Article Does o -Farm Migration of Female Laborers Inhibit Land Transfer? Evidence from Sichuan Province, China 1 ,y 2 ,y 1 1 1 , 3 , Kai Huang , Xin Deng , Yi Liu , Zhuolin Yong and Dingde Xu * College of Management, Sichuan Agricultural University, Chengdu 611130, China; hk666@stu.sicau.edu.cn (K.H.); lyx1@stu.sicau.edu.cn (Y.L.); zhuolinyong@stu.sicau.edu.cn (Z.Y.) College of Economics, Sichuan Agricultural University, Chengdu 611130, China; dengxin@sicau.edu.cn Sichuan Center for Rural Development Research, College of Management of Sichuan Agricultural University, Chengdu 611130, China * Correspondence: dingdexu@sicau.edu.cn y These authors contributed equally to this work and should be considered co-first authors. Received: 19 November 2019; Accepted: 7 January 2020; Published: 9 January 2020 Abstract: With the feminization of agriculture, the role of women in the rural land transfer market is becoming increasingly important. However, at present, there is little research focusing on the relationship between the o -farm migration of female laborers and land transfer rates. Using data on 1652 agricultural land plots owned by 232 rural households in Sichuan Province in 2014, IV-Probit (The Probit model of tool variable method is added) and IV-Tobit (The Tobit model of tool variable method is added) models were constructed to explore the relationships between o -farm migration and rural household land transfer (whether the rural households have land transfer-in and the area of land transfer-in by rural households) with consideration of gender. The results show that: (1) O -farm labor migration has a negative and significant impact on rural households’ land transfer-in rates. Under the same conditions, the o -farm migration rate increased by 10%, the probability of transfer-in land decreased by 2.6% on average, and the transfer-in area decreased by 2.7 mu on average. (2) The o -farm migration of female laborers inhibited land transfer-in rates. For every 10% increase in female labor migration, the probability of land transfer-in decreased by an average of 2.1%, and the land transfer-in area was reduced by an average of 3 mu (1 mu = 667 m or 0.067 ha). However, the impact of male labor migration on farmers’ land transfer-in is negative and not significant. This study provides a novel, gendered perspective to understand land transfer-in behaviors in hilly areas, which can provide further information on o -farm labor migration and the rational allocation of land resources. Keywords: land transfer; gender perspective; o -farm labor migration; Sichuan Province; China 1. Introduction Land and labor are the core elements of agricultural production. Farm output quotas are fixed on a household basis in the current system of rural land in China, implemented since the 1980s. It has greatly stimulated the productivity of rural households and rapidly developed the rural economy of China [1–7]. However, due to the restriction of the land quality equalization policy applied when land is contracted for production and assigned to households, cultivated land in the vast, hilly areas of China tends to be “small, scattered, and weak” [8]. With the development of the social economy, the small, scattered, and weak land-use problem has become increasingly prominent and has gradually become a major restriction to China’s rural economic development and food security [9–16]. With the continuous industrialization and urbanization of China, the household contract responsibility system, which Land 2020, 9, 14; doi:10.3390/land9010014 www.mdpi.com/journal/land Land 2020, 9, 14 2 of 14 features decentralized management, is increasingly unable to meet the needs of modern agricultural development, which is characterized by “marketization, scale, and informatization” [17]. It is generally believed in academic circles that the moderate scale of land management plays an important role in limiting land fragmentation. In such management, land transfer is an important method of realizing a moderate scale of land management [18–22]. Land transfer has e ects on the moderate scale management of land, raising rural household income, and preventing land abandonment [23]. Since the mid-1980s, Chinese governments at all levels have successively introduced a series of policies to encourage land transfer and promote the integration of rural land resources [24,25]. Although China has successively issued a series of policies to allow the transfer of “land-use rights” with compensation, the land transfer rate in China has not been high until now. For example, China’s land transfer rate was only 2.53% in 1999. Since the beginning of this century, with the implementation of a series of land policies (such as the “separation of three rights”), the size and form of land transfers in China have changed dramatically. The land transfer rate increased from 12% in 2010 to 37% in 2017, an average annual growth of 17.5% [26]. After 30 years of development of China’s land transfer market, although the transfer rate has increased significantly, it is still relatively low compared with those of other developed countries in Europe and North America, and is even lower than that in China in the last century. For example, the land transfer rate in the United States was 43% in 1992. In 1999, the land transfer rate in Uganda was 36% and, in the Philippines, it was 51% [27,28]. Sichuan is a large, mountainous province in China and a major agricultural province, and its land transfer rate has been lower than the national average. In Sichuan Province in 2016, an area of 19.703 million mu of rural land was transferred (1 mu = 667 m or 0.067 ha), accounting for 33.85% of the household contract management size, and less than the national average of 1.25%. The division of labor in rural households, especially o -farm labor migration, is one of the important causes of this low land transfer rate [29–31]. Since China’s reform and opening up, with the gradual elimination of policy barriers and the transformation of the economic structure, many rural laborers have migrated to cities to seek urban o -farm sector employment [32–34]. Since 1984, when China opened the door for rural residents to work in cities, the rural labor force has decreased while urbanization and industrialization have increased [35–40]. In 1978, the number of rural o -farm workers was 32 million. O -farm payrolls have grown faster since the mid-1980s, reaching 103 million in 1992 and 288 million by the end of 2018. In the 40 years from 1978 to 2018, the number of rural o -farm jobs increased by 257 million in absolute terms, an eight-fold increase [41]. This massive migration of the labor force has resulted in a fundamental structural transformation of the relationship between rural people and land. This not only alleviates the contradiction of “more people and less land” in China, but has also led to demands from political and academic circles for the reallocation of land resources [42]. O -farm labor migration has always been considered an important driver of rural households’ land use (including land transfers) [43,44]. However, inconsistent relationships between o -farm labor migrants and land transfer have been reported in the literature. According to the findings from previous studies, the correlation between the two mainly includes the following three aspects: (1) O -farm employment of the labor force promotes the transfer of rural households’ land. For instance, Deng et al. [45] reported an inverted U-shaped relationship between o -farm employment, land transfer behavior and land transfer size, with inflection points of 55.55% and 56.22%, respectively. Xu et al. [46] reported that o -farm employment encourages rural households to transfer out their land, while part-time employment has an inverted U-shaped relationship with land transfer. Yao et al. [47] reported that o -farm employment can promote the development of the farmland transfer market by increasing the farmland inflow of heterogeneous rural households. The higher is the o -farm employment rate of the rural labor force, the higher is the incidence of land transfer. (2) There is no causal relationship between o -farm employment and land transfer and, to some extent, it will inhibit the development of the land transfer market. For example, Chen et al. [48] reported that there is no causal relationship between the proportion of o -farm labor migration and the proportion of land transfer, and the two Land 2020, 9, 14 3 of 14 do not develop in unison. Qian [49] reported that, due to the increasing rate of rural part-time and agricultural feminization, and the increasing proportion of agricultural machinery inputs, o -farm employment does not accelerate the rate of land transfer. Ma et al. [50] reported that, due to the unique social security function of rural land, o -farm labor migrants often do not give up their land-use rights. (3) They both promote and restrict each other. For example, Li et al. [51] argued that, on the one hand, the migration of surplus rural laborers accelerates the speed of land transfer; on the other hand, due to the urban–rural dual structure, especially the household registration system, insucient o -farm labor migrants inhibit the eciency of land transfer. These above studies have laid a solid foundation with which to understand the correlation between o -farm labor migration and land transfer. However, few studies have focused on the impact of female labor migration on land transfer, especially the impact of female labor migration on land transfer-in, based on gender perspectives with land plots as the research scale. The present study analyzed the impact of female labor migration on land transfer from the perspective of behavioral decision-making of land transfer-in. The reasons for this arrangement are: (1) Under the current household contract responsibility system, the behavior decision of land transfer-in determines the realization of the moderate scale of land management. (2) Among the many factors that still a ect the land transfer level in China, the inhibiting e ect of female labor migration on land transfer-in may be important. Since women are expected to earn far less than men in o -farm employment and are easily burdened by housework, as well as the common divisions of labor that males engage in the o -farm sector and females in the farm sector and the traditional concept of “breadwinning men and homemaking women” in Chinese rural households [52–55], there is hysteresis in female o -farm labor migration and the feminization of agricultural production (the o -farm migration of the female labor force is lower than that of the male labor force). In 2001, 82.1% of rural women were engaged in pure agriculture, while on 64.7% of men. In 2017, 65.2% of migrant workers were male, and 34.8% female [56]. 2. Theoretical Analyses The New Economics of Labor Migration (NELM) was proposed by Stark in the 1980s. Its core idea is that rural households will rationally allocate their labor and land resources on the premise of maximizing family benefits and minimizing risks [57]. Based on this, the present study defined a theoretical model of rural households’ agricultural income maximization as: Y = Y1 Y2 (1) Y1 = XA + TS (2) Y2 = (X + DX)A + (T + DT)S (C + R) (3) In the above equations, Y is agricultural income maximization, Y1 is the family income before the transfer-in of rural households’ land, Y2 is the family income after the transfer-in of rural households’ land, X represents the amount of land contracted by rural households before land transfer-in, A represents the output per unit of land, and XA represents the household’s agricultural income. T is household o -farm employment time, S is the household o -farm employment wage rate, and TS is household o -farm income. DX represents the amount of land change after land transfer-in, DT is the change in o -farm employment time after land transfer, C is the cost of a land ( ) transfer transaction, and R is land transfer. The term X + DX A is household farming income after land transfer-in and (T + DT)S is the household o -farm income after the land transfer-in. If Y < 0, the rural households choose to transfer-in the land; if Y  0, the rural households choose not to transfer-in the land. At the 19th national congress of the communist party of China (CPC) in 2017, the “rural revitalization strategy” was established, which proposed to keep the land contract relationship stable Land 2020, 9, 14 4 of 14 and permanent, and extend it for another 30 years after the second round of land contracts expires [58]. China’s household contract responsibility system will remain unchanged in the long run. Due to the hysteresis of rural female labor migration, the proportion of women in agricultural production is gradually increasing and the female rural labor force has become the main component of rural market economic activities [59]. In 2016, 47.5% of China’s female labor force was engaged in agricultural production, and 52.5% were engaged in non-agricultural production. Theoretically, in a relatively closed environment, the development of technology is relatively slow in the short term and changes in capital input are relatively small. In this case, a certain amount of labor force corresponds to a certain size of land management. When the family labor force migrates for o -farm employment, the area of land that the family can manage decreases, which encourages them to transfer-out land that cannot be cultivated. In contrast, a relative surplus of labor will encourage households to transfer-in the land and expand the scale of production. Therefore, the o -farm migration of female rural laborer may a ect land transfer-in rates in the following ways: (1) When female rural laborers migrate o -farm, the family labor force is insucient and the willingness of rural households to transfer-in land is low. Moreover, as female laborers are the “fresh troops” of agricultural production in the context of agricultural feminization, their o -farm migration will inhibit land transfer-in more than that of men. (2) When female laborers choose to stay behind, it is usually because the expected income of agricultural production and the opportunity cost of o -farm employment are relatively high, and the remaining female labor force increases the family labor force, increasing the ability of rural households to engage in agricultural production. Then, there is an incentive to expand the scale of operation and increase agricultural income, thus they are more willing to transfer-in land. Based on the above theoretical analysis, the present study tested the following research hypotheses: Hypothesis 1 (H1). There is a negative impact of o -farm labor migration on land transfer-in (and the area transfer-in). Hypothesis 2 (H2). Female labor migration has more negative e ect on land transfer-in (and the area transfer-in) than male migration. 3. Data and Methods 3.1. Study Areas Sichuan province, an important exporter of labor to the rest of China and a typical agricultural province, is located in the southwest of China [60]. It covers 486,052 km and had a population of 91.13 million in 2017, of which the rural population was 59.97 million, accounting for 65.58%. Its GDP was 36,980 billion yuan, and its total agricultural output was 40.42 billion yuan. Since the mountainous and hilly terrain area of Sichuan province accounts for about 90% of the total area, the land is not conducive to large-scale agricultural operations [61,62]. 3.2. Data Sources The data used in this research mainly came from a household survey conducted in Guang yuan, Zigong, and Shehong districts (counties) of Sichuan Province, China, in April 2014. This survey used questionnaire-based face-to-face interviews of households, involving questions on family structure (labor force, numbers of elderly members and children, and o -farm payrolls), income (agricultural and non-agricultural income, household agricultural assets, total household assets, etc.), and land use (land transfer, land acquisition, land abandonment, and self-cultivated land). In terms of specific sampling methods, this study adopted with equal probability of selection within the stratum to generate samples. First, based on the studies by Cao et al. (2018), Luo et al. (2007), and Rozella et al. (1996) [63–65], with the per capita gross value of industrial output, 183 districts (counties) in Sichuan Province were divided Land 2020, 9, 14 5 of 14 into three groups. Then, one district (county) was randomly selected from each group to obtain three sample districts (counties). Second, by the same method, all the villages and towns in each sample area (county) were randomly divided into two groups. Third, two villages were randomly selected from each sample township according to their level and location of social and economic development. Finally, 20 rural households were selected randomly from each village by using the village roster and a random number table. Through the above process, questionnaires were obtained from 240 households. After logical screening, valid samples were obtained from 232 households, involving 1652 land plots. The e ective recovery rate of questionnaires was up to 97%. 3.3. Methods 3.3.1. Dependent Variable The dependent variable this study focused on was the transfer-in of rural households’ land, which was mainly measured from two aspects: (1) whether rural households have land transfer-in; and (2) the area of land that rural households transfer-in. 3.3.2. Independent Variable O -farm labor migration with consideration of gender was the independent variable studied in the present study. This study did not strictly distinguish between part-time and o -farm employment, but uniformly classified it as o -farm labor migration. This study mainly measured this by the following two aspects: (1) the impact of o -farm migration on land transfer-in; and (2) the impact of o -farm migration on land transfer-in area. Among them, when investigating the impact of o -farm labor migration on land transfer-in, the core independent variable was the household o -farm labor migration rate, which was measured by the proportion of the total number of o -farm employees and part-time employees in the total labor force. When discussing the influence on land transfer-in from the perspective of gender, the labor migration rate of each gender was used as the focus variable, which was specifically measured by the proportion of male and female o -farm employment and prat-time employment in total household labor force. To reduce the impact of missing variables on the research results, Deng et al. Mullan et al. and Xu et al. [47,48,66] were referred. In this study, the characteristics of the head of a household (such as age and educational level of the head of the household), family characteristics (including area of cultivated land per people, numbers of the elderly and children, whether there are farmers whose age is over 64 years old, the non-current assets of a family, agricultural non-current assets, etc.), and land plots features (such as the presence of irrigation, distance from home, massif terrain attributes, etc.) were included, as the control variables in the model [66,67]. 3.3.3. Method Selection Probit and Tobit models were adopted to explore the impact of o -farm labor migration on whether rural households have land transfer-in and the area of land transfer-in, in consideration of gender. R = + Migration + X + " (4) i 0 1 i i i A = + Migration + X + " (5) i 1 i i i where R and A represent the land transfer-in behavior of household i (whether land is transfer-in i i and the area of land transfer-in, respectively). Migration is the core independent variable of this research model (the proportion of rural labor o -farm migration, the proportion of male labor o -farm migration, and the proportion of female labor o -farm migration). The vector X represents the control variable, is a constant term, " is a disturbance term, and and are the coecients to be estimated 0 i 1 i for the related variables. Land 2020, 9, 14 6 of 14 In addition, due to the possible causal relationship between o -farm labor migration and land transfer-in, the core independent variables in this study may be endogenous. To solve the endogeneity problem in o -farm labor migration, this study set the mean ratio of o -farm labor migration to the total labor force in the same village except the survey households as the instrumental variable. That is: IV Migration = (Migration + Migration + ::: + Migration )/(n 1) Then, IV-Probit and IV-Tobit 1 2 n1 models were used to explore the impact of o -farm labor migration on land transfer-in incidence and area, respectively, to ensure robust results. The model formula was as follows: R = + IV Migration + X +  (6) i 0 1 i i i A = + IV Migration + X +  (7) i 0 1 i i i where the definitions of the variables are similar to those in Equations (4) and (5). The modeling process was conducted using the Stata 13.0 software program (StataCorp. LLC, College Station, TX, USA). 4. Results 4.1. Descriptive Statistical Analysis Table 1 shows the descriptive statistics of the variables involved in the models. The land transfer-in probability and scale were relatively small. Among the 232 sampled rural households, only 2% transfer-in the land. The mean area of the 1652 plots of transfer-in land was 0.01 mu. The per capita cultivated size of the land was 0.86 mu and the average distance from the plot to home was 0.61 km. The household heads were mainly middle-aged and elderly, with low levels of education. The average age of the household head was 58.19 years and the average length of education was 5.91 years. The o -farm labor migration rate was 54.52%, of which men comprised 33.25% and women 21.27%. Table 1. The definition and data description of the variables in the model. Variables Definition and Coding Mean SD Transfer-in Whether the rural households have land transfer-in (1 = Yes; 0 = No) 0.02 0.14 Area -in The area of land transfer-in by rural households (mu ) 0.01 0.12 Migration Labor migration/total household labor force (%) 54.52 28.71 Female-migration Female labor migration/total household labor force (%) 21.27 18.99 Male-migration Male labor migration/total household labor force (%) 33.25 20.44 Head age Age of household head (year) 58.19 10.37 Head edu Education level of household head (year) 5.94 3.4 Per size Per capita cultivated size (mu ) 0.86 0.68 Elder Child Numbers of elderly men and children in the family 1.47 1.14 Elder agri Whether there are elderly farmers > 64 years old (1 = Yes; 0 = No) 0.27 0.44 Fixed asset Household fixed assets (10,000 yuan ) 16.14 20.36 Agri asset Household agricultural fixed assets (10,000 yuan ) 0.38 0.68 Irrigation Whether the plot can be irrigated (1 = Yes; 0 = No) 0.46 0.5 Whether the households’ land has been confirmed the right to Right 0.87 0.34 contract (1 = Yes; 0 = No) Distance Distance from the plot to the home (m) 610.52 829.57 Location 1 Whether the plot is located on a plain (1 = Yes; 0 = No) 0.12 0.32 Location 2 Whether the plot is located on a mountain (1 = Yes; 0 = No) 0.82 0.39 Location 3 Whether the plot is located on a hill (1 = Yes; 0 = No) 0.06 0.25 a 2 b Note: 1 mu = 667 m or 0.067 ha; 1 US dollar = 6.119 Yuan in 2014. 4.2. Econometric Model Results 4.2.1. The Impact of O -Farm Labor Migration on Land Transfer-in Table 2 shows the impact of o -farm labor migration on land transfer-in. Among them, Models 1–5 show the results of the Probit regression model of rural household transfer-in incidence. Among them, Land 2020, 9, 14 7 of 14 Models 1 and 2 are the baseline regressions using the Probit model; Model 1 is the Probit regression including only core variables, while Model 2 includes control variables based on Model 1. Models 3–5 used IV-Probit, and Model 5 is the marginal e ect result obtained by the model. Similarly, Models 6–10 are regressions of the land transfer-in area model; Models 6 and 7 are Tobit baseline regressions, while Models 8–10 are the IV-Tobit models that included the instrumental variable. All models were significant at a level of p < 0.05, indicating that at least one independent variable in the model was significantly correlated with the dependent variable (Table 2). At the same time, the endogeneity test statistics of Models 3–6 and 8–10 were significant (p < 0.05), indicating that the core independent variable of the model was endogenous and the method of its use was correct. In terms of the impact of o -farm labor migration on rural households’ land transfer-in decisions, Migration negatively a ected rural households’ land transfer-in (p < 0.01) and the results were robust. All other things being equal, every 10% increase in Migration reduced the land transfer-in incidence by 2.6% on average. Migration was significantly and negatively correlated with the land transfer-in area (p < 0.05). With other conditions held constant, every 10% increase in Migration reduced the average transfer-in area by 2.7 mu. Looking at the impact of the other control variables on transfer-in of rural household land, the impact of Head age on Transfer-in was not significant. Head edu was negatively impacted on Transfer-in (p < 0.10). Per size, Right, and Distance were significantly negatively impacted on Transfer-in and Area-in. Agri assets and Irrigated variables were positively impacted on Transfer-in and Area-in. 4.2.2. The Impact of O -Farm Labor Migration on Land Transfer-in from the Perspective of Gender Table 3 shows the impact of O -farm labor migration on land transfer-in from the perspective of gender. Similar to Models 1–10, Models 11–15 show the results of the Probit regression model of whether rural households transfer-in the land. Models 11 and 12 are the benchmark regressions using the Probit model. Model 11 is the Probit regression model including only the core variables, while Model 12 includes the control variables as well. Models 16–20 show the results of the regressions of the area of transfer-in land; Models 16 and 17 are Tobit benchmark models, while Models 18–20 are IV-Tobit models that include the instrumental variable. All models were significant at p < 0.01, indicating that at least one independent variable in each model was significantly correlated with the dependent variable (Table 3). The endogeneity test statistics of Models 13–16 and 18–20 were also significant at p < 0.01, indicating that the core independent variable of each model was endogenous and the method of using the instrumental variables was correct. In terms of the impact of o -farm labor migration on rural household land transfer-in incidence and area, Female migration negatively a ected Transfer-in and Area-in (p < 0.01) and the results were robust. With other conditions held constant, every 10% increase in Female migration reduced Transfer-in by 2.1% on average and Area-in by 3 mu on average. Male migration was not correlated with Transfer-in. In terms of the impact of other control variables on land transfer-in, the impact of household head characteristics on land transfer-in were not significant. Per size, Fixed asset, Right, Distance and Fixed asset were significantly negatively impacted on Transfer-in and Area-in. Elder Child, Agri assets and Irrigated variables were positively impacted on Transfer-in and Area-in. Land 2020, 9, 14 8 of 14 Table 2. Results of the econometric model of the impact of o -farm labor migration on land transfer-in. Whether the Households Have Land Transfer-in The Area of Households’ Land Transfer-in Variables Model 1 Model 2 Model 3 Model 4 Model 5 Model 6 Model 7 Model 8 Model 9 Model 10 Migration 0.0069 *** 0.0101 *** 0.0141 ** 0.0328 *** 0.0026 ** 0.0130 *** 0.0121 ** 0.0247 ** 0.0487 ** 0.0027 ** (0.0014) (0.0031) (0.0056) (0.0041) (0.0012) (0.0048) (0.0059) (0.0121) (0.0191) (0.0012) Head age 0.4385 ** 0.2488 0.0195 0.5086 * 0.4153 0.0233 * (0.2110) (0.1853) (0.0131) (0.2987) (0.2963) (0.0126) Head age 2 0.0039 ** 0.0023 0.0002 0.0045 * 0.0038 0.0002 * (0.0018) (0.0016) (0.0001) (0.0026) (0.0026) (0.0001) Head edu 0.0722 ** 0.0491 * 0.0039 * 0.0763 * 0.0714 0.0040 * (0.0322) (0.0293) (0.0021) (0.0451) (0.0458) (0.0022) Per size 0.9409 * 0.6195 ** 0.0487 ** 0.9504 ** 0.8741 ** 0.0490 * (0.5024) (0.2929) (0.0245) (0.4614) (0.4135) (0.0265) Elder Child 0.2493 ** 0.2315 ** 0.0182 ** 0.2547 * 0.3325 ** 0.0187 ** (0.1147) (0.0948) (0.0086) (0.1500) (0.1630) (0.0086) Elder agri 0.0905 0.2072 0.0163 0.0038 0.3960 0.0222 (0.3921) (0.2931) (0.0248) (0.4127) (0.4847) (0.0249) Fixed asset 0.0246 * 0.0141 0.0011 * 0.0200 *** 0.0150 * 0.0008 (0.0126) (0.0093) (0.0006) (0.0076) (0.0079) (0.0006) Agri asset 0.4753 *** 0.2611 ** 0.0205 *** 0.4684 *** 0.3506 *** 0.0197 *** (0.1391) (0.1132) (0.0066) (0.1280) (0.1243) (0.0075) Irrigation 0.7780 *** 0.4218 ** 0.0331 *** 0.7973 *** 0.6011 ** 0.0337 *** (0.2683) (0.2117) (0.0120) (0.2627) (0.2495) (0.0130) Right 1.4091 *** 0.9264 *** 0.0728 *** 1.5786 *** 1.4498 *** 0.0813 *** (0.2017) (0.2170) (0.0172) (0.4892) (0.4630) (0.0140) Distance 0.0015 *** 0.0011 *** 0.0001 *** 0.0016 *** 0.0015 *** 0.0001 *** (0.0005) (0.0004) (0.0000) (0.0005) (0.0005) (0.0000) Location2 0.3558 * 0.2616 0.0206 0.4360 * 0.4402 * 0.0247 ** (0.2090) (0.1624) (0.0126) (0.2515) (0.2492) (0.0124) Location3 0.4074 0.2372 0.0186 0.4572 0.3747 0.0210 (0.2741) (0.2445) (0.0175) (0.3175) (0.3575) (0.0187) constant 1.7444 *** 11.0168 * 1.3063 *** 5.0303 3.1859 *** 12.8187 2.5491 ** 8.7084 (0.1020) (6.2265) (0.3999) (5.3869) (0.9033) (8.2971) (1.1107) (8.2222) Instrumental variables No No Yes Yes Yes No No Yes Yes Yes Wald  25.4173 *** 133.7751 *** 6.3579 ** 383.9628 *** 383.9628 *** 4.1382 ** 35.3192 *** 35.3192 *** 1.3043 ** 9.5047 *** 9.5047 *** 0.9126 ** 4.8353 ** 4.8353 ** Endogenous Wald N 1652 1652 1652 1652 1652 1652 1652 1652 1652 1652 Note: All numbers in parentheses are robust standard errors. Statistical significance at the 0.1, 0.05, and 0.01 level is denoted by *, **, and ***, respectively. Land 2020, 9, 14 9 of 14 Table 3. Results of the econometric model of the impact of o -farm labor migration on land transfer-in with consideration of gender. Whether the Households Have Land Transfer-in The Area of Households’ Land Transfer-in Variables Model 11 Model 12 Model 13 Model 14 Model 15 Model 16 Model 17 Model 18 Model 19 Model 20 Female-migration 0.0053 * 0.0019 0.0246 *** 0.0374 *** 0.0021 ** 0.0105 * 0.0068 0.0649 *** 0.0570 *** 0.0030 *** (0.0029) (0.0064) (0.0081) (0.0075) (0.0009) (0.0058) (0.0075) (0.0196) (0.0177) (0.0010) Male-migration 0.0081 *** 0.0165 *** 0.0286 *** 0.0107 0.0006 0.0133 *** 0.0157 *** 0.0744 *** 0.0255 * 0.0014 * (0.0025) (0.0046) (0.0037) (0.0089) (0.0005) (0.0044) (0.0052) (0.0132) (0.0132) (0.0008) Head age 0.4153 ** 0.2400 0.0133 0.4807 ** 0.3545 0.0189 * (0.2086) (0.1908) (0.0093) (0.2372) (0.2343) (0.0112) Head age 2 0.0037 ** 0.0021 0.0001 0.0043 ** 0.0032 0.0002 * (0.0018) (0.0017) (0.0001) (0.0021) (0.0021) (0.0001) Head edu 0.0826 *** 0.0453 0.0025 0.0694 * 0.0464 0.0025 (0.0313) (0.0340) (0.0016) (0.0379) (0.0427) (0.0024) Per size 0.9649 * 0.6868 ** 0.0381 * 0.9143 * 0.8243 * 0.0439 * (0.5355) (0.3031) (0.0212) (0.5040) (0.4485) (0.0242) Elder Child 0.2498 ** 0.2041 * 0.0113 * 0.3059 * 0.3289 ** 0.0175 ** (0.1211) (0.1108) (0.0064) (0.1591) (0.1654) (0.0077) Elder agri 0.1316 0.0479 0.0027 0.0594 0.2343 0.0125 (0.3976) (0.3140) (0.0173) (0.3821) (0.4249) (0.0231) Fixed asset 0.0219 * 0.0139 * 0.0008 * 0.0156 * 0.0119 0.0006 (0.0120) (0.0074) (0.0005) (0.0086) (0.0081) (0.0004) Agri asset 0.5189 *** 0.2835 *** 0.0157 *** 0.4649 *** 0.2910 ** 0.0155 ** (0.1497) (0.0939) (0.0055) (0.1233) (0.1210) (0.0066) Irrigation 0.7681 *** 0.5288 *** 0.0293 *** 0.7861 *** 0.6276 ** 0.0334 *** (0.2658) (0.1848) (0.0112) (0.2820) (0.2672) (0.0116) Right 1.4043 *** 1.1921 *** 0.0661 *** 1.5419 *** 1.5547 *** 0.0828 *** (0.2028) (0.1690) (0.0139) (0.3403) (0.3131) (0.0147) Distance 0.0015 *** 0.0012 *** 0.0001 *** 0.0014 *** 0.0014 *** 0.0001 *** (0.0005) (0.0003) (0.0000) (0.0005) (0.0005) (0.0000) Location2 0.3844 * 0.2630 0.0146 0.2698 0.2316 0.0123 (0.2104) (0.1762) (0.0099) (0.2174) (0.2181) (0.0130) Location3 0.4068 0.3523 0.0195 0.2938 0.3083 0.0164 (0.2716) (0.2384) (0.0130) (0.2638) (0.2926) (0.0156) constant 1.7395 *** 10.2268 * 1.7869 *** 5.5068 3.0188 *** 12.2274 * 4.8842 *** 8.0642 (0.1026) (6.1424) (0.3214) (5.4833) (0.5198) (6.8059) (0.4699) (6.7201) Instrumental variables No No Yes Yes Yes No No Yes Yes Yes Wald  25.4769 *** 147.8286 *** 108.7606 *** 211.5195 *** 211.5195 *** 36.3189 *** 68.1480 *** 68.1480 *** 274.3585 *** 24.8639 *** 24.8639 *** 140.2069 *** 44.3065 *** 44.3065 *** Endogenous Wald N 1652 1652 1652 1652 1652 1652 1652 1652 1652 1652 Note: All numbers in parentheses are robust standard errors. Statistical significance at the 0.1, 0.05, and 0.01 level is denoted by *, **, and ***, respectively. Land 2020, 9, 14 10 of 14 5. Discussion The present study focused on the impact of o -farm labor migration on rural households’ land transfer-in behavior, especially the impact of female labor migration on land transfer-in behavior. Micro survey data of 1652 agricultural plots owned by 232 rural households in hilly areas of Sichuan Province were used under the guidance of NELM theory. IV-Probit and IV-Tobit models were used to analyze the impacts of o -farm labor migration on land transfer-in incidence and area. The contributions of this study are as follows: (1) In exploring the impact of o -farm labor migration on land transfer-in, this study focused on the impact of female o -farm labor migration on land transfer-in. The use of a gender perspective is novel. (2) In exploring the impact of o -farm labor migration on land transfer-in, this study not only examined land transfer-in incidence, but also land transfer-in area, which is more comprehensive and practical. (3) The use of IV-Probit and IV-Tobit models e ectively dealt with the endogeneity problems existing in the models and made their results more accurate. There are some similarities and di erences between this study and previous ones. For example, consistent with [19,29,31,39,67,68] and other studies, o -farm labor migration was negatively correlated with land transfer-in incidence and area. However, unlike the above studies, and especially unlike the conclusion of [31]—that female migration has no significant impact on rural households’ land use—this study analyzed the impact of o -farm labor migration on land transfer from the perspective of gender and concluded that female migration inhibits land transfer-in more than male labor migration does. This may be because under the background of feminization and part-time employment of agriculture, women are the main participants in agricultural production activities and play an increasingly important role in family decision-making. This results in female migration having a greater inhibitory e ect on land transfer-in decision-making than male migration. In addition, the core independent variable setting of this study is di erent from the studies by [8,19,29,46]. This study did not strictly distinguish between part-time and o -farm employment, but classified part-time and o -farm employment as o -farm labor migration. Unlike the studies by [22,45] this study did not further explore whether there was a U-shaped relationship between o -farm migration and land transfer rates. Based on the above discussion and conclusions, we can draw the following policy implications. First, the government should actively complete the confirmation and registration of land ownership as soon as possible, reduce or give up a large number of administrative orders to intervene in land adjustment, keep the first household contract responsibility system unchanged, promote land “separation of three rights” (right to use, right to ownership, and contract right), and stimulate the development of the land transfer market. Second, the government should accelerate the development of rural vocational education and rural professional households and, especially, increase vocational skills training for women remaining in agriculture, to improve the human resources endowment of the female labor force and expand the scale of agricultural production. The government should improve rural social public services and reduce the female’ burden in housework and raising children so that the female labor force can have more energy to participate in rural market activities. Finally, the government should promote rural non-agricultural economic development to promote rural land transfer as well as to improve rural household income structures, increase the agricultural income proportion of household income, especially that of women, raise the economic status and decision-making power of women in the family, and keep the rural labor force in rural development. This study discussed the impact of o -farm migration on land transfer-in by rural households from a gender perspective. This provides a new perspective by which to understand the land transfer-in behaviors of rural households in hilly areas. However, this study has some shortcomings. For example, the influence of o -farm labor migration on land transfer is a dynamic process. This study only analyzed this relationship using cross-sectional data; future studies could use panel data to gain better insights. Additionally, this study only focused on the impact of o -farm migration on land transfer-in, but land transfer has two dimensions: transfer-in and transfer-out. Future studies could also explore the impact of o -farm labor migration on land transfer-out. Moreover, this study adopts the data from Land 2020, 9, 14 11 of 14 the field survey in 2014, which is relatively weak in timeliness. Future studies can be analyzed with the latest data. 6. Conclusions Based on the above analysis, this study drew the following three main conclusions: 1. There was a significant negative impact of o -farm labor migration on the land transfer-in incidence of rural households. Every 10% increase in o -farm labor migration reduced the probability of land transfer-in by 2.6% on average and the area of land transfer-in decreased by 2.7 mu on average. 2. From the perspective of gender, female migration had an obvious inhibitory e ect on land transfer-in. Specifically, for every 10% increase in the female migration rate, the land transfer-in probability decreased by 2.1% on average and the area of land transfer-in decreased by 3 mu on average. At the same time, there was no impact of male migration on rural household land transfer-in rates. 3. Other control variables, such as Head age, Head edu, Right, Per size, Agri asset, and Irrigation, all significantly impact on farmers’ land transfer behavior and area. Author Contributions: Data curation, K.H. and X.D.; Investigation, Y.L. and Z.Y.; Methodology, D.X.; Software, K.H. and Y.L.; Writing—original draft, K.H.; and Writing—review and editing, D.X. All authors have read and agreed to the published version of the manuscript. Funding: This research was funded by National Natural Science Foundation of China (Grant Nos. 41801221, 41571527, 41601614, and 41701622); Innovation training program of Sichuan Agricultural University in 2019 (2019106226105); and Undergraduate research interest cultivation program in 2020 of Sichuan Agricultural University (Study on the relationship between livelihood transformation and sustainable land use of farmers in mountainous areas of Sichuan province). Acknowledgments: We gratefully acknowledge financial supports from National Natural Science Foundation of China (Grant Nos. 41801221, 41571527, 41601614, and 41701622) and Innovation training program of Sichuan Agricultural University in 2019 (2019106226105). The authors also extend great gratitude to the anonymous reviewers and editors for their helpful review and critical comments. Conflicts of Interest: The authors declare no conflict of interest. References 1. De Brauw, A.; Huang, J.; Rozelle, S.; Zhang, L.; Zhang, Y. 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Published: Jan 9, 2020

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