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Explaining Inequality: Wealth Mobility, Inheritance,
and Extinction in Rural Japan 1694-1872
Yuzuru Kumon∗†
Draft Date: December 2018
Early Version: Please do not cite
Abstract
How important are inter-generational transfers in explaining inequality? I look at
the case of rural Japan, 1694-1872, a highly equal society in the early modern period.
Using inter-generational data on household land ownership in 30 villages, I explore three
channels through which land inequality was transmitted across generations: wealth
mobility, inheritance, and extinction. Consistent with the modern literature, I find
that higher levels of wealth mobility partially explains the relative equality of Japan.
Further, I explore how household formation and extinction was gradually changing
the household composition of the village. Partible inheritance was practiced by rich
households resulting in dispersion of wealth among the rich. Simultaneously, the poor
faced high probabilities of household extinction due to the lack of heirs which decreased
inequality. The latter two mechanisms have received little attention in the literature
but may have played a large role in sustaining the usual equality of early modern Japan.
∗Graduate Student at UC Davis, Department of Economics†This is a preliminary draft. Please do not cite.
1
The negative correlation between inter-generational mobility and inequality known as
the “Great Gatsby Curve” has shown that inter-generational transfers are a key component
in explaining inequality (Corak, 2013). Such transfers could occur through inheritance,
education, genetics, institutions or credit constraints (Adermon et al., 2018; Becker et al.,
2018; Boserup et al., 2016; Elinder et al., 2018; Sellars and Alix-Garcia, 2018). Alleviating
inequality seems to rest on policies that increase mobility; these may be inheritance taxes,
better education systems, or improved credit for the poor. However, the literature has been
lacking in two dimensions. Firstly the findings have been based on developed economies but
there is relatively little about whether intergenerational transfers matter to a similar degree
in agricultural societies. Secondly, the limitations in data have meant that we are focused on
tracking family lines rather than whole populations. Therefore, we do not know about how
the lack of heirs (household extinction) or the existence of multiple heirs were interacting
with mobility to change inequality over the long-run.
This paper uses a new dataset of village censuses across 30 villages in rural Japan, 1694-
1872, to investigate how wealth mobility, inheritance, and household extinction were affecting
inequality over the long-run. The data allows me to track household land ownership across
generations which is a extreme rarity within agricultural societies, and it is among the first to
do so within a developing economy. I find a negative correlation between wealth mobility and
inequality at the village level showing that the “Great Gatsby Curve” is a relevant framework
for thinking about agricultural economies. I also find evidence for unequal villages having
poverty traps which led to bi-modal landholdings and low wealth mobility. Such villages
practiced more capital intensive agriculture suggesting that capital constraints played a key
role in decreasing mobility.
However, this framework is also limited because mobility becomes difficult to define
for households that were newly created or for heir-less households that go extinct. This
is problematic if such cases are correlated with wealth. I find that new households were
commonly formed by the surplus sons of the rich who commonly inherited part of the family
land. This dispersed wealth among the rich and decreased inequality. This was the result of
a positive correlation between incomes and fertility during this era. On the flip side, the poor
were less likely to have heirs and I find a higher probability of their households going extinct.
This would decrease inequality. The poor were not missed when it came to inequality.
These findings have implications for the literature on wealth dynamics in developing
economies. The idea that poverty traps can cause inequality has received much attention in
the literature (Barrett and Carter, 2013; Zimmerman and Carter, 2003; Carter and Barrett,
2006), and the empirics have focused on finding cases of poverty traps in African economies
(Lybbert et al., 2004; Carter and Lybbert, 2012). I confirm that poverty traps were also
2
important in the historical case of Japan and it is not only a modern phenomenon. However,
the broad scope of this study also shows that poverty traps can coexist with regions of high
mobility and equality. The findings are suggestive of a geographic aspect to poverty traps
whereby regions with capital intensive agriculture tend towards high inequality while labor
intensive regions remain equal.
The rest of the paper is organized as follows. The first section explains the background of
the Japanese villages during the early modern period. The second section explains the data
source. The third section analyzes the effects of wealth mobility and inequality. The fourth
section analyzes the effects of partible inheritance and extinction on wealth distributions.
The final section concludes.
Background
The Japanese Villages
Tokugawa Japan (1600-1868) was an agricultural economy, with 60-70% of GDP being
agricultural.1 Of the total GDP, 30-35% was composed of land rents. The distribution of
land incomes was the primary source of inequality, and competing interests fought over land
rights. In this feudal economy, the main claim over land came from the 300 lords who were
given ownership over vast amounts of land by the Tokugawa shogunate, in return for various
services. Thus, the lords were the de jure owners of land, and had the right to extract land
rents in kind and in money. I call this income of the lord “taxation”. The lords and the
samurai class were separated from the rural economy because they lived in castle town due to
an institution known as Heino-Bunri. Therefore, the day-to-day maintenance of agricultural
land and the collection of these taxes was left to the mostly autonomous peasants.
In order to collect taxation, the lord had to clarify the liability for taxation and have a
broad understanding of the yield within the rural economy. To collect information, the lords
conducted large scale cadastral surveys of their lands in the early 17th century and recorded
the size and yield of all plots. Taxation was based on the estimated yield. Ultimately,
the village had to organize and collect the tax that was demanded by the lord and paid it
to the lord (Murauke-sei). To facilitate the distribution of tax within the village, a name
was attached to each plot in the cadastral survey (the Naukenin), and they were deemed
responsible for paying the taxation on the plot. However, if individual peasants could not
pay their share, others in the village had to compensate for the missing tax.
Within the village, the peasant whose name was attached to the plot was recognized as
1Saito and Takashima (2016)
3
Figure 1: The Japanese Feudal Economy in the Tokugawa Period
the de facto “owner”, and the lord would support the claim if any disputes arose. In general,
the lord did not interfere in the land distribution within villages, as long as taxes were paid.
From hereon, to differentiate between the land ownership of the lord and the peasant, I refer
to the peasant’s land ownership as landholdings. The peasant landholder was left with
many rights over there landholdings, including the sale or rent of the land and the claim
to all land rents that remained after taxation. I summarize the feudal economy using my
terminology in Figure 1.
Land distribution were always unequal to some degree resulting in some peasants hold-
ing more land than they could cultivate. To resolve this issue households either employed
servants or rented out their excess lands. Land rental markets were established in the early
Tokugawa period and were the favored solution to excess land by the end of the Tokugawa
period.2 By the 18th-19th century, these land rental markets were working efficiently and
Arimoto and Kurosu (2015) show that most if not all of the surplus in landholdings relative
to the family labor force were resolved by land rentals in Northeast Japan. Land sales were
also common and many plots frequently changed hands in the cadastral surveys.3 The ex-
istence of these markets imply two facts. First, land rights were secure enough to allow for
the sale of such rights. Second, the positive price attached to land show that the asset gave
the owners a positive stream of income implying that the lords had indeed failed to extract
2Takeyasu (1966) shows how various village records attach different names to the same plot within thesame year. He argues that this was due to the cultivator being different to the owner, suggesting the existenceof a land rental market.
3Takeyasu (1969) shows that land was frequently changing hands as early as the 17t century.
4
Figure 2: A representation of pre-industrial Inequality
all of the land rent as argued above.
The land holding peasant could collect large amounts of land income but many of these
households were still too poor to subsist purely on land incomes. All but the richest cultivated
land. Thus, the most common survival strategy by peasants was to cultivate the land they
owned (if any) and rent plots from others with a surplus to make ends meet.
The Determinants of Inequality
In the pre-industrial period wealth inequality was the driver of all inequality because labor
income was relatively evenly distributed. In these agricultural economies, skill premiums
were small with typical skilled workers in rural Japan earning perhaps 2.6 times more in
wages.4 Moreover, such skilled workers were rare. Hence, the labor’s share of income was
very equally distributed compared to the modern day and its inequality can be ignored. An
implication is that wealth inequality is a very good measure of total inequality making my
analysis of wealth inequality translate well to income inequality.
Thus, there were two channels through which inequality evolved (see figure 2). The first
were changes in the share of labor’s share of total income. This could be affected by huge
shocks, such as the black death (which did no hit Japan), after which wages are known to
have risen. In Japan, wages appear to have stayed low, meaning this was a fairly static
channel. The other channel was changes in the distribution of wealth. The focus of this
paper is the latter channel.
A blooming literature that estimates pre-industrial inequality has began to illuminate
the facts of pre-industrial inequality (see table ). Yet, relatively few papers have looked at
the determinants of inequality. Milanovic et al. (2011) argues that there was an “inequality
4Saito (2005)
5
Country Year Type Gini Prop. Landless Prop. Demesne% %
England* 1688 Wealth 84.8England* 1803 Wealth 86.5Sweden 1750 Wealth 0.72 20
Denmark 1789 Wealth 0.87 59Finland 1800 Wealth 0.87 71Spain* 1749-59 Land 0.78
NW. Italy+ 18th C. Wealth 0.77Western Pomerania 1556-1631 Land 24
Bohemia 1785-9 24Moravia 1785-9 12.8Hungary 1790 Land 27Poland 1600 Land 44Estonia 1800 Land 38-62
Central Russia 1765 Land 26-36China+ Qing Land 0.6-0.71 13-26China 1929-33 Land 17Japan 1700-1868 Land 0.52 11
Table 1: Wealth Inequality and Wages in Pre-industrial Countries* indicates estimates that include urban regions, whereas other countries include both urbanand rural. + indicates samples from a few villages.Sources: Eastern Europe is from Cerman (2012).
possibility frontier”, whereby inequality cannot be so high as to cause a subsistence crisis
among the poor. In particular, economies with GDP per capita at subsistence levels cannot
have high inequality. Thus, an argument can be made that inequality is positively correlated
with economic development. Yet, the causation could be the reverse with inequality affecting
the path of economic development, and remains to be fully investigated.5
The other classic argument has been the suitable environment for plantations and its
related institutions, in the case of Latin America, causing land to become unequally dis-
tributed.6 However, this argument lacks generality for explaining inequality in areas that
were not plantation economies. Overall, our theoretical understanding of the underlying
causes of the evolution of wealth inequality remains weak.
5For instance inequality has been associated with lower education in 19th century Prussia. See Cinnirellaand Hornung (2016)
6Frankema (2009)
6
Figure 3: The Stem Family in Japan
Data
I use panel data from the religious investigation registers (shumon aratame cho) of 30
villages in rural Japan. These were provided by the “Population and Family History Project”
at Reitaku University7, and by Kawaguchi Hiroshi who made the “DANJURO” dataset.
This data amounts to 1106 village-year observations and 67,056 household-year observations.
All of these households are linked across time, which is possible because households were
inherited by heirs across generations (see figure 3). Some households did go extinct, due to
the lack of heirs, but such events were rare with less than 10% across generations. On the
other hand, households could also “branch” into multiple households if there were multiple
heirs, although this was not always the case.8
These registers were compiled by all villages beginning in 1671 following orders from
the Shogun, to enforce the ban of Christians within Japan. The registers achieved this by
annually recorded the names, ages, and religion of all individuals9 living in the village at the
time the register was compiled, in order to confirm the absence of Christians. Two copies
of these records were made by village heads within each village, with one copy submitted to
the lord, and the other stored by the village head for future reference. Some copies of the
registers held by the village heads survived in storehouses, and these were later collected by
historians10.
7I thank Satomi Kurosu and her team, who gave me access to the data, and helped me to digitize partsof the data. I also thank the team of RAs at UC Davis, who helped me input the digitized version of thedata.
8More commonly, younger sons would work in cities or marry into other households.9However, infants/children were not included in some regions.
10Most of the copies held by lords appear to have been burned, due to the lack of storage space and old
7
The exact content of these registers varied by village and across time, or as administrative
norms changed. Some of these registers include information on landholdings of all households
within the village. Landholdings were measured in the yield value of the plot in units of
koku, where one koku was about sufficient to subsist one person for one year. Unfortunately,
there is only data for landholdings held within the village. I discuss this and other issue with
the data, namely the sampling of the villages, measurement error, and missing observations,
in detail below.
Sampling
Although there were over 70,000 villages at this time, I only have a sample of 30 villages.
The choice of these villages were dictated by data availability over the long-run. This means
I have focused on registers that recorded landholdings for over 25 years, and were linked
across time. Although 25 years is somewhat arbitrary, it should reflect changes in inequality
over multiple generations in the village, allowing it to capture long-run trends.
One source of bias in the data is through source survival. The survival of sources were
not random, with regions with paper scarcity or tea growing regions appearing to have
lower survival rates of registers.11 Also, the more powerful lords could implement their own
registration policies, and no sources have been found for the Satsuma, Choshu, and Tosa
domain in the west of Japan.
A second source of bias is through the decision to include landholdings within the regis-
ters.The inclusion of land depended on the lord who ruled over the village, and as certain
villages were transfered across different lords, the contents of the registers changed.12 Mat-
suura (2009) finds that 40% of registers that were collected in the province of Echizen, or
Fukui prefecture just north-east of Kyoto, included landholdings. The difference was driven
by the lord who administered the village, with the shogunate lands in particular having a
tendency to include landholdings.
Overall, there is a large regional bias in my sample (see table 2). All villages are from
Honshu island, the main island of Japan. Moreover, the observations are concentrated in a
handful of provinces, with more villages from Eastern Japan. It is possible to have included
a few more fishing villages, but they have been omitted due to the importance of alternative
types of wealth, such as boats. In such villages, landholdings would certainly be a poor
measure of wealth inequality.
registers having little administrative value.11For a detailed discussion of biases, see appendix 2 of Drixler (2013)12Due to the similarity in information with population surveys (ninbetsu aratame), which were also being
conducted at the time, many villages merged these two documents into one (shumon ninbetsu aratame cho),which increased the probability of including information on landholdings.
8
Regions Province Village YearsWest Mimasaka Hani 1816-1867
Iguchi 1775-1871Kougou 1767-1800
Yukinobe 1794-1870Central Mino Arioshinden 1752-1800
Higashi Fukase 1837-1865Nakasu 1789-1858
Niremata 1796-1855Nishijyou 1773-1872
Setsu Hanakuma 1789-1869Yamato Tsuji 1767-1869
East Hitachi Ariga 1739-1868Jikoku 1694-1856
Koozuke Hisaya 1763-1863Occhi 1817-1871
Yuzuruhara 1821-1861Musashi Karou 1834-1866
Kaminaguri 1804-1860Dodobashi 1826-1861
Shimoosa Sango 1840-1870Shimotsuke Kamiizumi 1765-1793
Kawagishi 1792-1871Northeast Dewa Koseki 1744-1770
Iwaki Kamiyukiai 1780-1864Mutsu Inazawa 1801-1866
Ishifushi 1752-1812Kanozu 1774-1867Takagi 1798-1837
Tochiyamakami 1843-1870Tonosu 1800-1859
Table 2: Villages in the DatasetNote: Not all years have data, as many (if not most) of the years are missing. Here, I referto the West as villages in the current day regions of Kyushu, Shikoku, or Chugoku. Centralrefers to the Kansai or Chubu regions. East refers to the Kanto region. North East refers tothe Tohoku region.
9
Region Gini Prop. Landless Prop. Wealth Prop. Wealth VillagesBottom 40% top 20%
Kyushu (West) 0.47 0.05 0.09 0.51 4Chugoku (West) 0.50 0.07 0.09 0.56 23Kinki (Central) 0.59 0.24 0.05 0.64 9Chubu (Central) 0.59 0.21 0.06 0.64 64
Kanto (East) 0.46 0.05 0.12 0.53 86Tohoku (Northeast) 0.41 0.11 0.14 0.48 22
Table 3: Landholding Inequality in All Regions of Japan, pooling all periodsI have denoted in brackets how these regions match with the regional groupings I have definedabove.
I can also compare the inequality levels of these villages with long-run data to data that
includes single-year snapshots of inequality in 208 villages across Japan. Table shows the
inequality levels by region, and I note that inequality in the 30 villages used in this paper
is similar to levels observed within these regions, with the exception of villages in central
Japan.
Measurement Error
The measures of the value of landholdings itself has measurement error, which can cause
problems for my analysis. There are two sources, the first is that the value itself became
outdated, and the second is that landholdings outside the village went unrecorded.
The first issue stems from the fact that cadastral surveys were conducted in the early
17th century, when the lords surveyed output in each plot within all villages. The lord
recorded the yield of each field in units of koku.13 This value was recorded on subsequent
documents as the value of the plot. However, surveys did not occur after this, and by the
18th to 19th century, which is the focus of this paper, the values were out of date. Peasants
had no incentive to record updated values, because the lord could use this information as
the basis of taxation. Thus landholding values only accurately recorded their value in the
17th century.14
Therefore, measurement error can occur through hidden increases in plot size (known as
nawanobi), or increased productivity. The first is known to have occurred through expansions
in fields, such that landholders recorded two areas: the official (honse) and real area (yuse).
13One koku is typically approximated to the food a person needs to survive for one year14The value of landholdings was usually copied from cadastral surveys (kenchi-cho), that were specifically
made to record peasant landholdings. Due to the claim over land being based on these records, it is unlikelythat miss-recordings happened.
10
The second is through increased productivity, which is estimated to have increased output
per area by 51% during the early modern period (1600-1868).15 The absolute value of land
certainly became unreliable as a measure. I use the value of landholdings as a relative value,
in which case land values must have increased at similar rates everywhere, so that they were
good measures of relative wealth holdings within the village.
The lack of data on landholdings outside the village is another shortcoming of the data. I
would expect any estimates of inequality to be biased downwards, as the richest households
most likely held disproportionately more land outside the village. However, most households
only held landholdings within the village so the bias should be small. I can check the degree
of the problem by looking at the proportion of land held by outsiders in 47 villages for
which outsider landholdings were also listed. The average was 15%, a small proportion
of land. The richest peasants were usually those who held land outside the village, so I
underestimate wealth at the top of the distribution. This causes a modest downward bias
in my Gini coefficient estimates.
Yet, the bias is probably limited because peasants owned most if not all of their land
within the village. This was partly due to less demand, despite the opportunities for risk
diversification. Owning land in another village was unattractive for buyers, due to increased
costs of monitoring it. Moreover, land was partially managed by village councils, of which
the owner would not be a member, giving the owner less control over the land, making it less
attractive.16 Moreover, supply was also limited due to a tax system that put responsibility
of tax collection on the village rather than landholding individuals. Thus, a misbehaving
outsider could jeopardize the tax collection of the village. Therefore, trusted villagers within
the village were given priority for purchasing lands.
Missing Observations
Due to the sources being old, and not necessarily being stored in the best conditions, about
2% of the household landholdings are missing. This is often due to bugs eating the paper,
leaving holes where the data is missing. Due to nature being the source of measurement
error, it is unlikely that missing observations are correlated with anything.
However, this remains a problem for measuring inequality, especially because Gini-
coefficients can be highly sensitive to missing observation. To see this, suppose the biggest
landholder with 50% of the land is missing in one year. This will cause Gini-coefficients
15Based on Miyamoto’s estimates in Hayami et al. (2004)16In a study of villages in Echigo province, there are case studies of holders of land in other villages had
difficulty pawning land, or had less autonomy over land use compared to villagers of that village (see chapter6 of Watanabe (1995)). Another example is from Mandai (2015) who shows that the proportion of bad debtsfrom tenants was higher for those living outside the village compared to those from within the village.
11
to plummet, resulting in huge measurement error. Other measures of inequality are also
affected, to varying degrees.
To deal with this problem, I take the weighted average of past and future observations,
to impute the value, using the formula below (where there is a missing observation at time
t).
landholdingsi,t =j
j + klandholdingsi,t−j +
k
j + klandholdingsi,t+k
To avoid any unrealistically long periods for imputation, I limit j, k ≤ 5. Some observations
still remain missing, and I have dropped all years for which missing observations are more
than 5% of total households.
12
Figure 4: Wealth Gini Coefficients for Western Japan
Figure 5: Wealth Gini Coefficients for Central Japan
13
Figure 6: Wealth Gini Coefficients for Eastern (Kanto) Japan
Figure 7: Wealth Gini Coefficients for Northeastern Japan
Inequality in Japanese Villages
To present the levels of inequality within these villages, I present the Gini-coefficients
from the Japanese villages in Figure 4-8. (I can also show other measures of inequality but
14
(1) (2) (3) (4) (5)All Regions West Central Kanto Northeast
Y eari,t/100 0.000977 0.0134 0.0529∗∗∗ -0.0133 -0.0481∗∗∗
(0.00876) (0.0160) (0.00867) (0.0160) (0.0170)
N 1015 205 355 226 217adj. R2 0.962 0.567 0.969 0.905 0.963
Standard errors in parentheses∗ p < 0.1, ∗∗ p < 0.05, ∗∗∗ p < 0.01
Table 4: The Time Trend of Inequality in Japanese RegionsThe dependent variable is Gini Coefficient. Each village is given equal weight in the regres-sion. Robust Standard Errors.
the main trends remain unchanged).17 Each of the squares present one observation. It shows
one limitations of my data which is that this is not a complete panel.
It is also immediately apparent that there is a lack of trend in much of Japan. I can go
further, and attempt to estimate a trend using the OLS specification below.
Giniv,t = βv + β1Y eari,t
100+ εv,t
The village fixed effect causes me to only look at within village trends.
I find that there is a positive trend in central Japan, if we narrowly focus on regions
of Japan. This region was known for high inequality, being the most advanced part of the
country, and located near the large cities of Osaka, Kyoto, and Nagoya. However, in all
other regions, there is no positive trend, and even a negative trend in the northeast which
contrasts with findings from pre-industrial Europe where there was a positive trend (Alfani,
2015; Alfani and Ryckbosch, 2016; Alfani and Ammannati, 2017).
Overall, there is no evidence of a trend in Japan and this is convenient because it is
suggestive that inequality was in equilibrium. With respect to my later analysis on household
landholding dynamics, I will not have to worry about the village as a whole moving towards
equilibrium which may cause distortions in how wealth mobility may relate to inequality.
A second surprise from the data is the heterogeneity in inequality outcomes across vil-
lages. Some regions had high inequality, while others remained low. There must have been
some factor causing certain regions to converge towards differing equilibrium. To explore how
far regional differences in inequality can be explained by intergenerational transmissions, I
will later leverage this variation across villages.
17Other measures of inequality are available upon request.
15
Figure 8: A Case of Low Wealth Mobility and Divergence
Does Wealth Mobility Explain Inequality?
What was the underlying mechanism behind differing levels of inequality? Were different
mechanisms at work in high inequality villages as opposed to low inequality villages? Al-
though I cannot identify a causal explanation through the analysis of household dynamics
using the linked registers, I can significantly narrow down the potential explanations.
In particular, I can see whether inequality is associated with lower wealth mobility and
in the extreme a poverty trap.18 This would cause low social mobility and the creation
of class structures of rich and poor. One can visualize this using figure 8, which shows
a wealth mobility function at differing landholding classes. There are three equilibria but
the central one is unstable. Households to the right of the central equilibria accumulate
land and converge towards the high landholding equilibria. Those below this threshold will
converge to the lower equilibria.19 If this were true, we would expect a bimodal distribution
of households split between the rich and the poor. Wealth mobility would be low as the poor
remain poor and the rich remain rich. This suggests a number of potential scenarios. One
could be a situation with dual technology choices such as the use of commercial fertilizers
against traditional fertilizers. Combining this with credit constraints that limit fertilizer use
to large landholding households, it is possible to show a poverty trap will exist. Another
18For a summary of the literature, see Kraay and McKenzie (2014) or Barrett and Carter (2013)19One empirical case study of this is by Lybbert et al. (2004) who finds a poverty trap in the case of
Ethiopian pastoralists.
16
Figure 9: A Case of High Social Mobility and Convergence
valid hypothesis could be a nutritional trap where the poor are simply less productive due
to nutrition.
A contrasting case is one where all households are converging towards a single equilibria,
as shown in figure 9. This means there is one optimal point of landholdings, and households
are clustered around this point. Any households that are knocked away from this point will
quickly re-converge, meaning there is high wealth mobility. In the extreme case of perfect
wealth mobility the only cause of inequality are temporary shocks that reshuffle landholdings
over the short-run. For instance, the death of the breadwinner can lead to temporary sales
in land but an eventual recovery in the next generation.
There are two potential approaches to this analysis, parametric and non-parametric, both
of which are explored
A Parametric Approach
Using a simple model of wealth mobility, I estimate how wealth mobility affects inequality.20
Suppose
ln(wealthi,t) = α + βln(wealthi,t−k) + ε
20One example is Clark and Cummins (2015)
17
where β is the intergenerational elasticity. A higher number indicates lower wealth mobility.
If the economy is in equilibrium,
var(ln(wealthi,t)) =var(ε)
1− β2(1)
Hence, the equilibrium inequality is higher with larger degrees of shocks (a large var(ε)) or
lower levels of wealth mobility (a high β). It must be noted that when β = 1 inequality
levels will explode because there is no equilibrium due to the perfect memory of shocks.21
However, such imperfect wealth mobility have never been observed and should not concern
me here. To investigate whether it was wealth mobility driving inequality I estimate the
following specification.
IHS(landi,t) = αv,t + βIHS(landi,t−k) + γInequalityv,t−k × IHS(landi,t−k) + εi,t (2)
where IHS is the inverse hyperbolic sine function (IHS), and β measures the elasticity of
wealth across k years. Note that the IHS is similar to the natural logarithm, except it allows
for zeros which are common in this data.22 The IHS creates a more linear function close to
zero.23 It converges towards the natural logarithm function for larger numbers.24 As the
standard landholding unit of koku is small (less than one) for many households it will distort
the specification away from elasticities. Therefore, I use the unit of to which is one tenth of
a koku.
I can choose any k, but I will primarily use k = 30, which captures the average number
of years between generations. However, due to the lack of registers that are exactly 30 years
apart, I use years in the range of 25 ≤ k ≤ 30 and impute the implied landholdings for
k = 30.25 I use a village time fixed effect to absorb any fixed effects. The coefficient β is the
degree of wealth mobility. I expect γ to be positive if increased inequality is correlated with
decreased wealth mobility.
My unit of analysis is the household because the basic economic production unit was the
household at this time. Moreover, land was owned by the household and was inherited by
21This implies that the distribution of land in each period is the compound of all past shocks. A shockwith any distribution causes infinite variance as time tends to infinite.
22The other workaround is the make a log(x + constant) type specification. However, the choice of unitand constant becomes critical. For instance if we choose log(x+ 0.1), a household going from 0 to 0.1 unit oflandholding sees a large increase compared to choosing log(x + 1) where there is a negligible increase. Thisleads to an arbitrary choice of a believable % increase in landholdings.
23This may be sensible, if one believes that small increases in landholdings from zero should be treatedlinearly, rather than some arbitrary large or small increase when using a log(x + constant) specification.
24More accurately, it converges towards IHS(x) = ln(2) + ln(x), so that the slope is the same25I assume that households would have had a linear relationship in landholdings across time to impute the
value. However, I have zero as the lower bound of land holdings, so there are no negative values.
18
All Villages Gini < 0.4 0.4 ≤ Gini ≤ 0.8 0.8 < GiniOut-Migration or Extinction 4.0 2.9 2.4 10.1
In-Migration 0.9 1.1 1.0 0.2
Branch Households 9.2 4.7 9.2 14.0
Observations 2936 558 1814 564
Table 5: The percentage composition of unobserved households, by village inequality level
Figure 10: Unobserved Observations
surviving members. Such units were mainly composed of family members although agricul-
tural servants would also be incorporated into the household at times. This unit of analysis
departs from the literature on social mobility which focus on individuals.26
One issue is household churn from movements in/out of the village or branching of house-
holds (see figure 5). Ignoring these households can lead to selection bias. In the case of
branching, whereby households split into the main and branch household, I assume both
households had the same landholdings as their parent’s generation.
Another issue is those that are truly unobserved (see figure 10). This is due to in/out-
migration or extinction. This happened in about 4% of cases. I cannot distinguish extinctions
and out-migrations in the data. If I assume leavers are similar to those who migrate in, I find
the median person moving into my village sample had zero land suggesting those households
have zero landholdings in the next period. Similarly out-migrants are disproportionately
26Individuals could potentially have very different outcomes compared to households. However an insightfulpaper by Kurosu and Ochiai (1995) suggests downward mobility was the norm for individuals.
19
(1) (2) (3) (4) (5) (6)
IHS(Landi,t−30) 0.292∗∗ 0.532∗∗∗ 0.360∗∗∗ 0.465∗∗∗ 0.560∗∗∗ 0.498∗∗∗
(0.127) (0.125) (0.101) (0.0755) (0.0672) (0.0558)
IHS(Landi,t−30) ∗Ginii,t−30 0.526∗∗∗ 0.212 0.424∗∗∗
(0.176) (0.166) (0.139)
IHS(Landi,t−30) ∗ CVi,t−30 0.0989∗∗∗ 0.0550∗∗ 0.0733∗∗∗
(0.0328) (0.0224) (0.0197)Famine No Yes Both No Yes Both
N 1440 1471 2911 1440 1471 2911adj. R2 0.532 0.640 0.590 0.531 0.642 0.591
Standard errors in parentheses∗ p < 0.1, ∗∗ p < 0.05, ∗∗∗ p < 0.01
Table 6: Inequality and MobilityCV denotes coefficient of variation. Robust standard errors. Villages are equally weighted.
from the poorest households. Thus, I assume they have zero landholdings.
The results are presented in table 6. There is a clear correlation between inequality
and intergenerational wealth mobility, whether I use the Gini coefficient or the coefficient
of variation. Going from an equal village in the data with a Gini coefficient of 0.3 to an
unequal village with a Gini coefficient of 0.8 increases the coefficient by 0.21. The results
are not explained by differing degrees of attenuation bias between the equal and unequal
regions as the difference in attenuation is less than 1% given my earlier estimates of the
measurement error.27 Since some of the data includes periods of famine one may worry
that this can distort mobility estimates. Therefore, if I only look at non-famine data, the
increase is higher at 0.26.28 Thus, the decrease in wealth mobility is extremely high. The
coefficient during famine becomes insignificant in the case of Gini coefficient, but remains
somewhat significant when using CV as the measure of inequality. These findings are robust
to using a specification with the natural logarithm (see Appendix table 9). One problem
with the results in table 6 is that the sample of villages in the famine and non-famine years
are different. This is advantageous, because I can look at a wider variety of villages and
have more power. However, if I limit the regression to the 11 villages for which both famine
and non-famine are observed, I can see if there are different dynamics during these different
times.
The results are shown in table . The magnitude of effects are similar during non-famine
27This is true even if I double my estimate of standard deviation of error to 28% of the value of land.28I define this as when the village does not see a famine from t− 30 to t
20
(1) (2) (3) (4) (5) (6)
IHS(Landi,t−30) 0.316∗∗ 0.738∗∗∗ 0.556∗∗∗ 0.438∗∗∗ 0.673∗∗∗ 0.556∗∗∗
(0.143) (0.155) (0.104) (0.0815) (0.0955) (0.0597)
IHS(Landi,t−30) ∗Ginii,t−30 0.520∗∗∗ -0.0592 0.184(0.190) (0.203) (0.141)
IHS(Landi,t−30) ∗ CVi,t−30 0.125∗∗∗ 0.0113 0.0647∗∗
(0.0352) (0.0403) (0.0266)Famine No Yes Both No Yes Both
N 708 791 1499 708 791 1499adj. R2 0.654 0.658 0.661 0.659 0.658 0.663
Standard errors in parentheses∗ p < 0.1, ∗∗ p < 0.05, ∗∗∗ p < 0.01
Table 7: Inequality and Mobility for Villages with data for both Famine and Non-famineYears.CV denotes coefficient of variation. Robust standard errors. Villages are equally weighted.
years, but the effect during famines are zero. Moreover, all villages appear to experience
an equal and low level of wealth mobility, with a coefficient of approximately 0.7. This is
suggestive of famines disrupting land markets and decreasing wealth mobility.
A Non-parametric Approach
The weakness of the parametric approach is that I assume a linear relationship between
past and future landholdings. However, the literature for modern day African societies have
found very different outcomes by wealth class. If there is some kind of poverty trap, I would
expect the poor and rich to have different rates of wealth mobility. Thus, an alternative
specification is the following.
IHS(Landholdingsi,t) = f(IHS(Landholdingsi,t−30) + εi,t
I estimate this using local polynomial smoothing. An issue is that landholdings have to have
the same value in all villages due to the regression looking at local effects at each landholding
level. This was not the case due to differing agricultural environments or tax rates. Yet,
single village regressions will lack power. Instead, I focus on regions that had similar socio-
economic environments namely the equal northeast and the unequal mino region of central
Japan.
I drop all branch households because they often got significantly less landholdings than
21
Figure 11: Wealth Mobility in Northeast Japan: No Branch Households
the main household and they need to be distinguished from the main household who had
differing dynamics. The results are given in figures ?? to 12. The land distribution of these
regions are available in the appendix.
It is immediately clear that in the equal northeast of Japan there was convergence towards
3 units of IHS land which was 1 koku of landholdings. This is approximately half of the
land a man could cultivate with his labor.29 The households below 3 units of landholdings
would rapidly converge towards this point, whereas richer households had a slower downward
convergence.30 This seems consistent with the actual distribution being concentrated just
above 3 units. Branching did not affect this regions mobility.
In contrast, the households in Mino province of central Japan had a much lower point of
convergence, at 1 IHS unit of land, or approximately 0.1-0.2 koku of land. This was about
one tenth of what a man could cultivate with his labor, suggesting they were renting most
of the land that they cultivated. Moreover, there was much more rapid downward mobility
for those above this landholding causing all households to be caught in a poverty trap. For
the rich, landholdings appear to stabilize at about 55 koku of landholdings which was an
immense amount of land requiring perhaps 27 men to cultivate.
These findings could be consistent with two mechanisms. The first is a mechanism based
on two technologies; one technology does not require capital and a second technology requires
29Assuming 2 koku per man30We can ignore the right edge of the graph, due to the lack of power at high levels of landholdings.
22
Figure 12: Wealth distribution in Mino Province, Central Japan: No Branch Households
capital (see figure ). Only farmers with sufficient capital or wealth can access this technology
due to borrowing constraints. Thus, there are two equilibria, A and B. Only household with
sufficient wealth to bring them beyond the switch point can converge towards B. Hence,
there is sharp downward mobility between A and the switch point as observed in the data.
This is consistent with the narrative that the central regions near the huge cities of Osaka,
Kyoto, and Nagoya used large amounts of fertilizer. This is likely due to demand for cash
crops such as cotton from being close to cities. Many plots were known to have been double
cropping, whereby two crops were cultivated in one year, and this required large amounts of
fertilizer to quickly replenish the soil. This was done in order to meet the demands of the
cities. The proximity to cities also had the advantage of having sufficient supply of fertilizer
from cities in the form of dried fish and night soil. Geographically, it was efficient for capital
intensive agriculture to be located near cities.
Within the qualitative literature, it has been found that fertilizer could take up 43%
of household expenditure.31 Such cultivation methods required huge amounts of wealth or
borrowing which must have been advantageous for rich households. On the other hand, such
conditions did not exist32 in northeast Japan and this may have resulted in one technology
and one equilibrium.
The other mechanism, which could have been simultaneously occurring, was that cottage
31Imai and Yagi (1955) 10432There is at least nothing in the qualitative literature that suggests widespread fertilizer use in this region.
23
Figure 13: Agricultural Production with Two Technologies
industry opportunities were more prevalent in the central region which were the centers of
commerce. Thus, the land poor households may have had other forms of wealth or skills
with which they could make up for their lack of wealth. Thus, they were content with being
landless households.
This dataset does not allow me to distinguish between these two mechanisms, and these
remain as hypothesis to study in future work.
Partible Inheritance and Extinction
Although wealth mobility was a significant factor in generating inequality, it fails to
capture changes in household composition. This is problematic if changes in household
composition were not random with respect to wealth. I focus on how household extinctions
(the disappearance of households from villages) and the formation of new households through
partible inheritance affected household wealth composition.
The positive correlation between incomes and fertility suggest household extinction would
be more common among the poor. Indeed, the poor were known to have difficulty finding
marriage partners and were less likely to have heirs. Extinctions rarely happened due to the
deaths of all household members. Instead it occurred due to households becoming non-viable
as economic units. For instance, a household with little landholdings and no laborers would
collapse as household members left the village for relatives.
One special factor which acted in favor of the rich were adult adoptions, as it prevented
the lack of biological heirs leading to extinction. In an insightful paper, Kurosu and Ochiai
24
Figure 14: Effects of Changes in Household Composition to Inequality
(1995) shows that almost no rich households went extinct due to adoptions. Despite the
roughly 17% chance that a household would have no male heir33, the social mechanism of
adoption allowed rich households to overcome biological barriers to household continuation.34
Against initial intuition, the lack of extinction among the rich due to adoption will
decrease inequality. This is due to the nature of inheritance for heir-less households. If the
landholdings go to a near relative in the event of the household having no heir, this leads
to the consolidation of wealth into the relative’s household. In contrast, the continuation of
rich households prevents wealth consolidation.
In the case of partible inheritace, a positive correlation between wealth and partible
inheritance would lead to lower inequality. This is because the rich are dispersing wealth
across households while the poorer households can sustain their wealth levels. The qualita-
tive literature suggests this was true, as a law limiting partible inheritance (bunchi seigen
rei) attempted to ban partible inheritance, except for land rich households35, effectively pro-
moting this mechanism. Figure 14 summarizes the effect of changing household composition
on inequality.
To estimate the effects of these mechanisms, I estimate the following specification,
Yi,t = βv + β1IHS(Landholdingsi,t−30) + β2IHS(Landholdingsi,t−30) ∗ inequalityi,t−30 + εi,t
33If one assumes 5 children with a 40% chance of death before adulthood.34This may have also caused more poor households to go extinct, as their sons got poached away. I thank
Fabian Drixler for pointing this out.35The definition of land rich differed by region, but a commonly stated threshold is 10 koku
25
Extinction Partible Inheritance(1) (2) (3) (4) (5) (6)
IHS(Landi,t−30) -0.143 -1.036∗∗∗ -0.527∗∗∗ 0.341 1.306∗∗∗ 0.758∗∗
(0.220) (0.308) (0.162) (0.369) (0.439) (0.299)
IHS(Landi,t−30) ∗Ginii,t−30 -0.232 0.764∗ 0.175 0.110 -1.027∗ -0.404(0.402) (0.409) (0.251) (0.534) (0.580) (0.409)
F-test for joint significance 8.36 34.92 44.55 21.43 28.46 44.41(p-value) (0.02) (0.00) (0.00) (0.00) (0.00) (0.00)
Famine? No Yes Both No Yes Both
N 499 946 1445 1389 1357 2746
Standard errors in parentheses∗ p < 0.1, ∗∗ p < 0.05, ∗∗∗ p < 0.01
Table 8: The Effect of Landholding on Household Inheritance & ExtinctionsA Logit Regression, with the marginal effects at the mean
where Yi,t denotes branching, partible inheritance, or extinction. Partible inheritance is
defined as cases in which branch households36 are observed with land in period t. I estimate
this using Probit or Logit regression. I expect β1 +β2 to be positive for partible inheritance,
and negative for extinctions.
The results for the logit regression are presented in table 37. Note that the sample size
changes due to some villages having no extinctions or partible inheritance. There is a general
negative correlation between landholdings and extinction but with an apparently larger effect
during famines. The overall effect is huge with the marginal effect of landholdings at the
mean being a 43% reduction in going extinct when looking at the whole sample38.
In the case of partible inheritance there is a positive correlation as expected. The effects
seem to be stronger during periods with famine. Again, the interaction term is not strongly
significant. The marginal effect at the mean is large with a 55% probability increase in
partible inheritance39. The inequality interaction term is never strongly significant showing
both mechanisms functioned uniformly across Japan and decreased inequality everywhere.
To get a sense of the magnitude of these effects, I plot the marginal effects of landholdings
by bin in Figure 15. It is clear that extinction was a small threat to the rich while at least
15% of the poorest household went extinct across each generation. In addition, partible
inheritance was also practiced predominantly by the rich who would split their wealth among
36branch households are all households that branched between t and t-3037The results using a probit regression are almost the same. See the appendix.38Assuming a household in a village with a Gini coefficient of 0.539Assuming a household in a village with a Gini coefficient of 0.5
26
Figure 15: The Marginal Effect of Landholdings on Extinction (Top) and Partible Inheritance(Bottom)
27
multiple households at least 12% of the time while such cases were rare among the poorest.
The large magnitudes of these effects suggest this mechanism played a key role in reducing
inequality everywhere.
Conclusion
This paper is the first study that finds the “Great Gatsby Curve” relationship between
inequality and mobility in a pre-industrial economy. Much of the differences in inequality
across Japan can be explained by differing mobility patterns. In turn, the differing mobility
patterns appear to be explained by regional specialization in differing types of agriculture.
Areas near cities focused on capital intensive cash crops while the rural periphery focused on
labor intensive grains. Overall, mobility remains a key factor in explaining inequality among
agricultural societies.
The other big contribution has been to show that partible inheritance and extinction
could play a large role in inequality outcomes over the long-run. During an era in which
incomes and fertility were positively correlated, the extinction of the poor and the partible
extinction of the rich acted to reduce inequality within Japanese villages. If we compare
these findings to England circa 1600, extinction among the rich happened at least 20% of
the time among the richest households. This led to near relatives, who were also likely rich,
getting large transfers of wealth and increased inequality. This may partially explain why
Japan was a relatively equal society in the pre-industrial world. One implication is that
comparing differences in inheritance and extinction in addition to social mobility may give
us a more comprehensive idea of why inequality differs across societies.
Finally, the condition that favored equality in Japan was the positive correlation between
income and fertility but what would happen after the fertility transition. The implication
appears to be that there will be a reversal in effects with the rich going extinct and the
poor practicing partible inheritance leading to upward pressures on inequality. This could
be detrimental for growth if inequality affects education levels, as argued by De La Croix
and Doepke (2003). Could policies to decrease fertility in developing economies increasing
inequality and damage the chances for growth? This is a potential topic for future research.
28
Appendices
Alternative Specifications
(1) (2) (3) (4) (5) (6)
ln(Landi,t−30) 0.328∗∗∗ 0.569∗∗∗ 0.403∗∗∗ 0.481∗∗∗ 0.580∗∗∗ 0.515∗∗∗
(0.123) (0.118) (0.0976) (0.0735) (0.0642) (0.0544)
ln(Landi,t−30) ∗Ginii,t−30 0.480∗∗∗ 0.170 0.371∗∗∗
(0.172) (0.160) (0.136)
ln(Landi,t−30) ∗ CVi,t−30 0.0931∗∗∗ 0.0496∗∗ 0.0686∗∗∗
(0.0321) (0.0220) (0.0196)Famine No Yes Both No Yes Both
N 1440 1471 2911 1440 1471 2911adj. R2 0.542 0.683 0.607 0.542 0.684 0.608
Standard errors in parentheses∗ p < 0.1, ∗∗ p < 0.05, ∗∗∗ p < 0.01
Table 9: Inequality and Mobility, using natural logarithmRobust Standard Errors. Villages are equally weighted
Extinction Partible Inheritance(1) (2) (3) (4) (5) (6)
IHS(Landi,t−30) -0.0739 -0.546∗∗∗ -0.289∗∗∗ 0.178 0.619∗∗∗ 0.373∗∗∗
(0.120) (0.141) (0.0850) (0.172) (0.209) (0.139)
IHS(Landi,t−30) ∗Ginii,t−30 -0.121 0.415∗∗ 0.118 0.0477 -0.504∗ -0.208(0.207) (0.188) (0.127) (0.249) (0.272) (0.189)
F-test for joint significance 9.46 41.96 49.07 23.74 27.74 47.24(p-value) (0.01) (0.00) (0.00) (0.00) (0.00) (0.00)
Famine? No Yes Both No Yes Both
N 499 946 1445 1389 1357 2746
Standard errors in parentheses∗ p < 0.1, ∗∗ p < 0.05, ∗∗∗ p < 0.01
Table 10: The Effect of Landholding on Household Inheritance & ExtinctionsA Logit Regression with marginal effects at the mean
29
Wealth Distributions
Figure 16: Wealth distribution in Northeast Japan
Figure 17: Wealth distribution in Central Japan, Mino Province
30
References
Adermon, A., Lindahl, M., and Waldenstrom, D. (2018). Intergenerational wealth mobility
and the role of inheritance: Evidence from multiple generations. The Economic Journal,
128(612):F482–F513.
Alfani, G. (2015). Economic inequality in northwestern italy: a long-term view (fourteenth
to eighteenth centuries). The Journal of Economic History, 75(4):1058–1096.
Alfani, G. and Ammannati, F. (2017). Long-term trends in economic inequality: the case of
the florentine state, c. 1300–1800. The Economic History Review, 70(4):1072–1102.
Alfani, G. and Ryckbosch, W. (2016). Growing apart in early modern europe? a comparison
of inequality trends in italy and the low countries, 1500–1800. Explorations in Economic
History, 62:143–153.
Arimoto, Y. and Kurosu, S. (2015). Land and Labor Reallocation in Pre-Modern Japan: A
Case of a Northeastern Village in 1720-1870. IDE Discussion Paper.
Barrett, C. B. and Carter, M. R. (2013). The economics of poverty traps and persis-
tent poverty: empirical and policy implications. The Journal of Development Studies,
49(7):976–990.
Becker, G. S., Kominers, S. D., Murphy, K. M., and Spenkuch, J. L. (2018). A Theory of
Intergenerational Mobility. Journal of Political Economy, 126(S1):S7–S25.
Boserup, S. H., Kopczuk, W., and Kreiner, C. T. (2016). The role of bequests in shaping
wealth inequality: Evidence from danish wealth records. American Economic Review,
106(5):656–61.
Carter, M. R. and Barrett, C. B. (2006). The economics of poverty traps and persistent
poverty: An asset-based approach. The Journal of Development Studies, 42(2):178–199.
Carter, M. R. and Lybbert, T. J. (2012). Consumption versus Asset Smoothing: Testing the
Implications of Poverty Trap Theory in Burkina Faso. Journal of Development Economics,
99(2):255–264.
Cerman, M. (2012). Villagers and Lords in Eastern Europe, 1300-1800. Palgrave Macmillan.
Cinnirella, F. and Hornung, E. (2016). Landownership concentration and the expansion of
education. Journal of Development Economics, 121:135–152.
31
Clark, G. and Cummins, N. (2015). Intergenerational wealth mobility in england, 1858–2012:
Surnames and social mobility. The Economic Journal, 125(582):61–85.
Corak, M. (2013). Income Inequality, Equality of Opportunity, and Intergenerational Mo-
bility. Journal of Economic Perspectives, 27(3):79–102.
De La Croix, D. and Doepke, M. (2003). Inequality and Growth: Why Differential Fertility
Matters. American Economic Review, 93(4):1091–1113.
Drixler, F. (2013). Mabiki: infanticide and population growth in eastern Japan, 1660-1950,
volume 25. Univ of California Press.
Elinder, M., Erixson, O., and Waldenstrom, D. (2018). Inheritance and Wealth Inequality:
Evidence from Population Registers. Journal of Public Economics, 165:17–30.
Frankema, E. (2009). Has Latin America always been unequal?: a comparative study of asset
and income inequality in the long twentieth century, volume 3. Brill.
Hayami, A., Saito, O., and Toby, R. P. (2004). The Economic History of Japan: 1600-1990:
Volume 1: Emergence of Economic Society in Japan, 1600-1859. Oxford University Press.
Imai, R. and Yagi, A. (1955). Hoken Shakai no Noson Kozo. Yuhikaku.
Kraay, A. and McKenzie, D. (2014). Do poverty traps exist? assessing the evidence. Journal
of Economic Perspectives, 28(3):127–48.
Kurosu, S. and Ochiai, E. (1995). Adoption as an heirship strategy under demographic
constraints: A case from nineteenth-century japan. Journal of Family History, 20(3):261–
288.
Lybbert, T. J., Barrett, C. B., Desta, S., and Layne Coppock, D. (2004). Stochastic
wealth dynamics and risk management among a poor population. The Economic Journal,
114(498):750–777.
Mandai, Y. (2015). 19 seiki zenhan no jinushikeiei to kosakuninhensei. Shakai Keizai Shigaku,
81(1):69–93.
Matsuura, A. (2009). Shihai keitai to shumon aratame cho kisai: Echizen koku wo chushin
ni. Shodai Ronshu, 60(4):125–140.
Milanovic, B., Lindert, P. H., and Williamson, J. G. (2011). Pre-industrial inequality. The
economic journal, 121(551):255–272.
32
Saito, O. (2005). Wages, inequality and pre-industrial growth in japan, 1727-1894. Living
standards in the past, pages 77–97.
Saito, O. and Takashima, M. (2016). Estimating the shares of secondary-and tertiary-sector
outputs in the age of early modern growth: the case of japan, 1600–1874. European Review
of Economic History, 20(3):368–386.
Sellars, E. A. and Alix-Garcia, J. (2018). Labor Scarcity, Land Tenure, and Historical Legacy:
Evidence from Mexico. Journal of Development Economics, 135:504–516.
Takeyasu, S. (1966). Kinsei Hokensei no Tochi Kozo. Ochanomizu Shobou.
Takeyasu, S. (1969). Kinsei Kinai Nogyou no Kozo. Ochanomizu Shobou.
Watanabe, T. (1995). Kinsei Beisaku Tansaku Chitai no Sonraku Shakai: Echigokoku Iwa-
temura Satoke Monjyo no Kenkyu. Iwata Shoin.
Zimmerman, F. J. and Carter, M. R. (2003). Asset smoothing, consumption smoothing
and the reproduction of inequality under risk and subsistence constraints. Journal of
Development Economics, 71(2):233–260.
33