nonfamily living and the erosion of traditional family orientations among young adults
TRANSCRIPT
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Nonfamily Living and the Erosion of Traditional Family Orientations Among Young
Adults
Author(s): Linda J. Waite, Frances Kobrin Goldscheider and Christina Witsberger
Source: American Sociological Review , Vol. 51, No. 4 (Aug., 1986), pp. 541-554Published by: American Sociological Association
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NONFAMILY LIVING AND THE EROSION OF
TRADITIONAL FAMILY ORIENTATIONS
AMONG YOUNG ADULTS*
LINDA J. WAITE FRANCES KOBRIN GOLDSCHEIDER
The Rand Corporation Brown University
CHRISTINA WITSBERGER
The Rand Corporation
Young adults in recent cohorts have been leaving the parental home earlier and marrying
later now than they did several decades ago, resulting in an increased period of independent
living. This paper explores the consequences of time spent in non-family living, using data
from the National Longitudinal Surveys of Young Men and Young Women. We expect that
experience in living away from home prior to marriage will cause young adults to change
their attitudes, values, plans, and expectations, and move them away from a traditional
family orientation. We find strong support for this hypothesis for young women; those who
lived independently became more likely to plan for employment, lowered their expected
family size, became more accepting of employment of mothers, and more non-traditional on
sex roles in the family than those who lived with their parents. Non-family living had much
weaker effects on young men in the few tests that we could perform for them. The paper also
addresses the conditions under which living away increases individualism, and it discusses
the implications of these findings.
Beginning with the 1950s, the living arrangements
of American adults have been undergoing major
changes. More and more unmarried adults are
living apart from their immediate families, forming
non-family households' at a rate that far exceeds
the growth in the adult population. During the
1970s, non-family households increased 73 percent
while family households increased only 13 percent
(U.S. Bureau of the Census, 1980). This develop-
ment can be seen as a further extension of the
changes accompanying modernization that have
resulted in a decline in the centrality of the family.
Many have argued that this process may have
accelerated over the past several decades, as
indicated by a series of demographic changes,
including rising ages at marriage, falling propor-
tions of the population ever marrying, declining
fertility and particularly marital fertility, the
sizeable proportion of marriages expected to end in
divorce, and the large numbers of children living
with only one parent for at least part of their
childhood (Westoff, 1978; Davis, 1982; Espenshade,
1985).
Wth these changes have come substantial
changes in attitudes toward family life. For
example, recent surveys show increasing accep-
tance of divorce, permanent singleness and child-
lessness (Thornton and Freedman, 1982). Changes
in attitudes are normally explained by changes in
the social structure. However, it is also possible
that these effects are reinforced for individuals by
their own experiences, causing further shifts in
their family-related attitudes and behavior. Life
course theory predicts that this would be particu-
larly likely for experiences early in life-in
childhood or early adulthood. Other things equal,
parental divorce increases the likelihood of divorce
for children (Pope and Mueller, 1976), teenage
parenthood is more common among daughters of
teenage mothers (Baldwin and Cain, 1980),
number of siblings positively affects own actual
and expected family size (Terhune, 1974; Waite and
Stolzenberg, 1976) and children raised in non-
intact families are less likely to marry at all but
very young ages (Kobrin and Waite, 1984).
In this context, perhaps the most critical
characteristic of the rapid increase in non-family
households is its concentration among very young
adults. While non-family households increased
their share of U. S. households from 15 to 22
percent between 1960 and 1975 over all ages, the
comparable increase for households with heads age
25 or less was from 13 to 30 percent (Frey and
Kobrin, 1982). Young adults are leaving the
parental home substantially earlier now than they
did in the past. In Rhode Island, for example, the
American Sociological Review, 1986, Vol. 51 (August:541-554) 541
* Please address all correspondence to Linda J. Waite,
Senior Sociologist, The Rand Corporation, 1700 Main
Street, P.O. Box 2138, Santa Monica, CA 90406-2138.
The research reported here was supported by Contract
No. NOI-HD-12814 from the Center for Population
Research, National Institute of Child Health and Human
Development. We would like to thank Lee Lillard, Julie
DaVanzo, and the members of the Rand Population
Research Center Workshop for helpful comments.
l Non-family households consist of an individual
living alone or with unrelated persons.
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542 AMERCANSOCOLOGCAL REVEW
percentage of sons still at home at age 26 dropped
from 50 percent for those who had reached that age
between 1930 and 1950, to 20 percent for those
reaching that age between 1976 and 1979. The
comparable decline for daughters was from 37 to
13 percent (Goldscheider and LeBourdais, 1986).
When the trend toward earlier nestleaving
began, it was associated with declining marriage
age. However, it now is increasingly combined
with delays in marriage, with the result that more
and more young people are spending an important
part of early adulthood in a context in which family
roles may be much less salient, and are developing
tastes and skills that are likely to reduce their
orientation to family roles. The transition to
adulthood for recent cohorts is following a
distinctly different pattern from that of their
parents, and could well have a substantial
influence on their later lives. We have already
documented that the experience of non-family
living leads to a postponement of marriage, at least
for women (Goldscheider and Waite, 1985). But
does it have an influence on the kinds of marriages
eventually formed through its effects on expecta-
tions about the balance of work and family roles? It
is these influences that we wish to explore.
BACKGROUND AND HYPOTHESES
The centrality of family formation in all societies
results in well-defined norms, rooted in an
underlying sexual division of labor, norms that
traditionally lead women to orient themselves more
toward family roles than do men. In the United
States the proper ages at which to marry and bear a
first child are normatively well defined, and clearly
differ for men and women, allowing men more
time to acquire adult levels of independence and
autonomy (Ryder and Westoff, 1971; Rindfuss and
Bumpass, 1978; Modell, 1979). Scanzoni (1975)
found that marriage, work, and fertility are
strongly associated with sex-role norms: women
who defined themselves through traditional female
roles married earlier, were less likely to be
employed full-time or to use effective contracep-
tion, and expected to bear more children than
women with a more non-familial orientation. He
sees sex-role modernity primarily as an emphasis
on individualism (although he makes this equation
reluctantly), and summarizes his results by conclud-
ing that The greater the individualism, the less
the familism (p. 187).
Family-related norms clearly affect the behavior
of individuals; they may also respond to that
behavior, as Marini (1984) argues. In either case,
it is important to establish how such attitudes are
formed and altered by experience. Although some
researchers postulate that family-related norms are
laid down early in life (Blake, 1972; Gustavus and
Nam, 1970; Hoffman and Wyatt, 1960), other
researchers have emphasized how experiences
outside the family can induce changes in these
family-derived values and tastes. Mason (1974)
has argued that a role hiatus between the
traditional role of daughter and the traditional roles
of wife and mother gives young women an
opportunity to develop tastes for roles alternative
to motherhood-especially employment-that as a
result alter family formation. Rubin (1976) cites
impressionistic evidence that the rigidity of sex
roles in working-class families may result from
early marriage and men's lack of experience in
living independently of women-either mother or
wife-whose role it was to care for their physical
needs. This suggests that a role hiatus may also
affect young men's sex-role traditionality.
Spitze (1978) tested the role hiatus hypothesis
with longitudinal data, and found that those
women who attended college increased their
preference for employment, whereas those who
worked increased their preference for full-time
work in the home. However, a great many who
work or attend college after high school remain in
the parental home (Goldscheider and DaVanzo,
1985). Non-family living prior to marriage may
provide a more complete hiatus, and lead to
changes in the family-related attitudes, plans and
expectations of young men and women.
We test this proposition by examining young
women's plans for employment over the long run,
their total expected family size, the number of
children that they feel is an ideal family, men's and
women's attitudes toward the employment of
mothers under various conditions, and two dimen-
sions of global sex-role attitudes. Together these
measures reflect many aspects of young adults'
orientation to family versus individual concerns. In
these analyses, we hold constant their earlier plans'
and attitudes, measured-to the extent possible-
prior to any exposure to non-family living.
However, we show as well that omitting such
controls does not bias the results observed, since
the likelihood of non-family living in early
adulthood is not strongly related to underlying
work and family attitudes.
Specifically, we test the following propositions:
-The experience of non-family living during
early adulthood affects the attitudes, values,
and plans of young adults, compared with the
levels measured before the experience, and
moves them away from a traditional family
orientation.
-Living away from home has stronger effects
on personal plans and expectations than on
more global ideals, although the latter may be
affected as well, presaging normative change.
-Non-family living will have stronger effects
on the attitudes, expectations, and plans of
women than of men, since more of a role
hiatus is expected for men, even under
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ONAMLYLVNG543
traditional sex-role regimes, but non-family
living may affect men's views as well.
-Nonfamily living interacts with education past
high school to alter attitudes, expectations and
plans. Both attending college and living away
from parents influence young adults, but those
who go away to college change their views
more than those who go to college while
living at home.
-Those with more family-oriented attitudes are
not less likely to live away from home during
early adulthood than others, so that effects of
non-family living will not change greatly with
the addition or omission of controls for
attitudes, expectations or plans at time one
(prior to the risk period for nonfamily
living).2
DATA AND METHODS
Data for this analysis come from the National
Longitudinal Surveys of Young Women and
Young Men. Conducted by the Ohio State
University Center for Human Resource Research,
these surveys include information over a recent
15-year period on more than 10,000 young men
and women. Personal interviews were conducted
with national probability samples of the non-
institutionalized population of females age 14 to 24
in 1968, and males age 14 to 24 in 1966. Those
included responded to lengthy interviews in many
of the succeeding years through the early 1980s.3
Attrition from the sample over the panel period has
been relatively low; three-fourths of the original
Young Women's sample was re-interviewed in
1978, and seventy percent of the original Young
Men's sample was re-interviewed in 1976. These
are the last years used here.
The analysis reported in this paper uses as
control variables measures of stable respondent
characteristics, such as race and characteristics of
the parental family, taken at the initial survey
(1966 for the Young Men, 1968 for the Young
Women). Independent variables measuring the
respondent's current situation-for example, em-
ployment, education or marital status-were mea-
sured contemporaneously with the dependent
variable. Most models incorporate two measures of
the relevant attitudes, plans, or expectations: one
measured at the beginning of the period and one
measured later and used as the dependent variable.
Our sample is restricted to those age 14 to 17 in the
first year of the survey to allow us to observe and
measure a complete history of non-family living
prior to marriage.4 Thus, we have data on Young
Women from 1968 through 1978, and on Young
Men from 1966 through 1976; each group was 24
to 27 years old at the last interview analyzed here.
The outcome measures include a wide range of
young adults' family- and sex-role-related atti-
tudes, plans, and expectations. First, young
women were asked in each survey year about their
plans to work at age 35, as an indicator of long-run
plans for employment. We divided this measure
into (a) those who planned to work and (b) those
who planned not to or were undecided.5 Second,
we include two measures of fertility asked in 1971,
1973, and 1978: young women's expected family
size and the number of children that they think is
ideal for a family. Expected family size was
measured from questions on children already born
and additional children expected in the future.
Taken together, these questions cover the primary
roles-mother and worker-that young women
must balance during their adult lives.
Third, we examine three measures of respondents'
views about the proper ways that mothers in
general should balance work and family roles;
these are all scales. One of these, called attitude
toward mothers' working, consists of the sum of
responses to three questions (coded as five-point
Likert scales) about the conditions under which the
respondent thinks that married mothers of pre-
school children may work, given that a trusted
relative is available for child care: (1) if she needs
the money; (2) if she wants to and her husband
agrees; and, (3) if she wants to but her husband
doesn't particularly like it (see Appendix). The
points from these three items were summed into a
single scale which ranges from 3 (traditional) to 15
(liberal).6 Young Women answered these questions
2 If early attitudes and non-family living are not
strongly related, then eliminating early attitudes from the
equation for later attitudes does not introduce specifica-
tion bias; hence, where early and later attitudes are
strongly related, lack of change in the coefficient for
non-family living when early attitudes are added or
dropped indicates that young adults' likelihood of living
away from home does not vary with their early attitudes.
3 The NLS Young Women were interviewed annually
from 1968 through 1973, again in 1975, 1977, 1978, the
Young Men annually from 1966 through 1971, and again
in 1973, 1975, 1976, the last years that we use in the
analysis reported here.
'Preliminary examination of the available data
showed that none of the young women, and only a few
young men, lived away from home before age 18. Since
the initial survey did not ask about prior years' living
arrangements, we could not know if those older than age
17 at the first survey had already experienced some years
of non-family living.
5 Specifically, the young women were asked what kind
of work they would like to be doing when they are 35.
Coded responses were: a) married, keeping home, raising
a family; b) same as present job; c) don't know; and d) an
occupation other than their current one.
6 For each of the three questions, five points were
assigned the response definitely all right, and one
point to definitely not all right. The mid-point
response was undecided. Although these three items
comprise a formal Guttman scale, we report results for a
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544 AMERCANSOCOLOGCAL REVEW
in 1968, 1972, and 1978; the Young Men did so in
1971 and 1976.
Finally, two more general indices of sex-role
attitudes were included in the 1972 and 1978
Young Women's interviews (see Appendix). These
were Likert-type questions, also coded as five-
point scales. The questions overlap to a substantial
extent in the two years but are not identical. They
deal with the impact of women's employment on
their families, and include value judgements about
appropriate roles for men and women. The
variables used in our analyses are the composite
indices (or factor scores) derived from the
coefficient matrix of a factor analysis done with
oblique rotation. Our factor analysis of each of the
series produced two distinct dimensions. One,
which we called sex-role attitudes (Family),
reflects the importance of women's time at home to
their children and families. The second dimension,
sex-role attitudes (Jobs), measures views of the
importance of women's employment to their
self-esteem and to the economic well-being of their
families. A higher score indicates greater accep-
tance of non-familial roles for wives and mothers.
Finding two distinct dimensions of sex-role
attitudes in this series of questions replicates
results from a number of other studies. Mason and
Bumpass (1975) and Mason et al. (1976) found,
using questions overlapping to some extent with
those that we use, that respondents answered
relatively consistently all questions on the appro-
priateness of the traditional division of labor within
the family, and those on rights of the sexes in the
labor market, but apparently saw little need to
connect their views across these two dimensions.
Our key indicator of non-family living is the
proportion of the years that the respondent lived
outside the parental family between age 17 and
first marriage or the terminal date for the analysis,
whichever occurs first.7 Non-family living could
include years spent in a college dormitory, military
barracks, living with roommates of either sex and
living alone. This measure uses the proportion of
potential years of non-family living actually away
from home, rather than the number of years, to
control for the differences between individuals in
the potential number of years. Since all respon-
dents in our sample were living at home and
unmarried as of the first interview, only those who
married at age 18 had an opportunity to live away
from home prior to marriage.
One disadvantage of the use of proportion rather
than number of years is that the smaller the number
of potential years of non-family living, the easier it
is to have spent either all or none of it actually
away from home. If we assume that individuals
have an underlying propensity to live away from
home, then we have fewer observations on this
propensity for individuals with a small number of
potential years away. This gives us inefficient but
unbiased estimates of these underlying propensities
for these individuals.
The use of proportion rather than number of
years away implies that the first year of non-family
living has a larger effect than subsequent years,
with the effect of each year declining at a rate of
(years - 1)/years, a slow to moderate decay
function. This function makes sense theoretically,
as we expect that the new experiences a young
adult undergoes by living away, as well as the new
skills acquired, are largest in the first year, with
additional skills and experiences added at a
declining rate with more years of non-family
living.
One could argue, alternatively, that family living
should include both time living with parents and
time living with a spouse. Just as young people
may decide to leave the family to live away, so
they may decide to form a new family of their
own. This argument implies a specification of
proportion of potential years of non-family living
spent actually away, that includes in the denomi-
nator all the years from age 17 until the measure of
the dependent variable, including years after
marriage, since the person could have lived away
those years if he or she had not married. We
created such a measure and include a discussion of
it in our results.
We measure living arrangements for respondents
using the household listing available in each survey
year. This gives the relationship to the respondent
of all individuals living in the household, their age,
sex, and certain other characteristics. Thus, we can
summated rating scale of the items, as described above,
to preserve maximum information about the respondents'
views toward employment of mothers. However, we
repeated all analyses after coding the items into a
Guttman scale. We created this scale with two alternative
coding schemes, either including or eliminating the
undecided category as a pass. Both scales performed
comparably. This Guttman scale has a coefficient of
reproducibility ranging from 0.97 to 0.99 for the Young
Women in 1968, 1972, and 1978, and a coefficient of
scalability varying between 0.81 to 0.94 for the same
years. For the Young Men, the Guttman scale on the
same items has a coefficient of reproducibility of 0.97 in
both years, and a coefficient of scalability of 0.85 and
0.87 in 1971 and 1976, respectively. Thus, the scales
appear to have identical-and excellent-measurement
properties for Boys and Girls.
7 This measure reflects the respondent's living arrange-
ments at the survey date, the only time for which we have
information about this variable. Living arrangements for
young adults have never been measured-to our
knowledge-at less than one-year intervals. We assume
relatively little change between survey dates in family vs.
non-family living. We weighted survey years to reflect
the actual amount of time between surveys.
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ONAMLYLVNG545
identify those respondents who reside with parents
and those who live away at the survey date.8
We have also included as controls other
variables that are likely to affect the family- and
sex-role-related plans and attitudes of young
adults. These include family background character-
istics (socioeconomic status and family structure)
measured at the initial survey, and current
socioeconomic and family characteristics, mea-
sured in the same year as the dependent variable.
Table 1 presents definitions, means, and standard
deviations of all independent and dependent
variables.
Our analytic strategies vary depending on how
often and in which years measures of the
dependent variables were obtained. One measure,
work plans, was asked of the young women in
every survey year. The first response to this
question, asked when the young women were 17
years old, provides a Time 1 baseline before any
non-family living could occur from which we
measure change. Plans for work at age 35 stated at
later ages are the dependent variable. We arbi-
trarily selected these later ages to be 20, 22, and 24
years old, at periods of 3, 5, and 7 years after the
first measure, based on questions answered for
20-year-olds between 1971 and 1973; for 22-year-
olds between 1973 and 1975; and for 24-year-olds
between 1975 and 1978. This portion of the
analysis provides the strongest test of our hypoth-
eses, in that work plans prior to any experience of
non-family living can be fully controlled. Compar-
ing the effects of non-family living with and
without controlling work plans at age 17 tests the
importance of controlling them.
The second set of dependent variables includes
those measured only occasionally. These are
expected and ideal fertility, attitudes toward
mothers who work under certain specific condi-
tions, and the more global set of questions on
sex-role attitudes (Family and Jobs). For these
dependent variables we modified our analytic
strategy to use the later measure as the dependent
variable, with the earlier measure included as an
independent variable to provide an approximate
baseline. Thus, in our analysis of fertility expecta-
tions and ideal fertility, we predict 1973 expecta-
tions and ideals (when the young women were
aged 19 to 22) from 1971 expectations and ideals
(when they were 17 to 20), plus characteristics and
experiences of the individual. This latter analytic
strategy does not always allow us to measure the
attitude in question before any experience with
non-family living. We test the importance for our
conclusions of this limitation.
For clarity, we have included a brief table that
gives the ages of the young women and the survey
years included for various outcome measures. The
young men were ages 24 to 27 when we measured
their attitudes toward mothers' work in 1976.
Equations with continuous dependent variables,
including both measures of fertility and all the
attitude scales, are estimated with ordinary least
squares. Equations for work plans, a dichotomy,
use logistic regression, estimated with maximum-
likelihood techniques (Goodman, 1976). To permit
comparison of the effects of the independent
variables across equations, we transformed the
logit coefficients to yield measures analogous to
unstandardized ordinarily least squares (OLS)
regression coefficients (Hanushek and Jackson,
1977). The transformed logit coefficients reflect
the estimated effect of a unit change in the
independent variable on the probability of planning
to work at age 35, evaluated at the sample means.
RESULTS
We discuss the results of the analyses described
above as they provide evidence on each of the
hypotheses presented earlier. We begin with the
first and most general hypothesis-that nonfamily
living changes young adults' plans, expectations
and attitudes about family and work roles away
from a traditional family orientation. Before we
discuss the individual models, however, we must
note the strikingly consistent picture that emerges
across the wide range of measures analyzed for
females: living away from parents tends to alter
young women's attitudes, expectations and plans
toward non-familial roles. The more experience
that young women have with independent living,
the more they change their plans for later work,
their family size expectations, their attitude toward
work by mothers, and their family-related sex-role
attitudes away from a traditional family orienta-
tion. In contrast, no significant effects appear in
the one analysis possible for young men, although
the coefficients have the expected sign.
Turning to the detailed results, we see in Table 3
that after controlling for young women's plans for
employment as reported when they were 17 years
old, the higher the proportion of years lived away
from parents between age 17 and the age in
question (or first marriage, whichever came first),
the greater the likelihood that the young women
planned to work at age 35. This effect is large and
significant for age 20, although it attenuates in size
with increasing age, suggesting that the effects of
non-family living may be short-lived. The coeffi-
cients imply that a young woman who lived away
all of the time between age 17 and 20 or her
marriage (whichever came first) was about 10
percentage points more likely to plan for later
employment, net of her plans stated only 3 years
8 For further details, on measures of living arrange-
ments available from these data see Goldscheider and
Waite (1985) and Goldscheider (1985).
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546 AMERCANSOCOLOGCAL REVEW
Table 1. Description of Independent Variables Used in the Analysis*
Means (standard
deviations for
continuous variables)
Nonfamily living Proportion of years spent in non-family living between .199
age 17 and first marriage or age in question (.309)
Work 35 at 17 (D) Plans to work when age 35 as measured at age 17 .416
Back(D 0=Whte andotherraces .299
Non-Intact (D) Did not live wth 2 natural parents at age 14 .186
Parents Education Average years of school competed 10397
byprens 3225
outhD Cenus regon396
Size of Labor Scale ranging from1 (rural) to 8 3.431
Force in Area (urbanzed areas of 3 mllion or more) (2.356)
YearYearbecam age inquestion74.019
(1.001)
EducationYears of schoolingcomleted12581
(2.189)
Enrolled(D Enrolledinschool ful-tim .119
Empoyed (D) Current full-time or part-time empoyment .573
usbands total income In 1967 constant dollars (thousands) 2.504
(3.664)
Mrried (D) Currently married for the first time .466
Divorced (D) Currently divorced, separated, or wdowed 062
Remrred(D Currentlyremrred.014
Kds (D Livngwthownchldren.368
Emloyed*kds Interactionterm.132
Standard deviation
(for continuous
Dependent Variables Means variables)
Plans to hold a job at age 35
(I=yes, 0=no):
ag20551
ag22554
ag24652
Attitude toward mothers working
(3 to 15, high = more liberal):
Girls
196897332577
1972106822400
Boys
1971106722926
1976117852780
Sex-role attitudes (Family)
(-2.9 to 1.6, high = more liberal):
972005875
978025923
Sex-role attitudes (Jobs)
(-2.3 to 1.8, high = more liberal):
1972 008711
1978 003715
Expected family size
(in children, 0 to 13):
197125091561
197319491253
Ideal family size
(in children, 0 to 14):
197129441251
197326201130
(D) Dummy variable.
* The statistics for the independent variables come from the Young Women's sample at age 22.
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NONAMLYLVNG547
Table 2. Ages and Years Measured for Young Women
urveyYars Aes
Work Plans Attitude toward
at Ages: Mothers Wrkng Fertility Sex Roles
ge n1968 20 22 24 1972 1973 1978
14 1978
5197319751977 18-21 19-22 2427
16 1972
17 1971 1973 1975
No surveys were done in 1974 or 1976.
earlier, compared with a woman who did not live
away during this period.9
The analysis of young women's attitudes toward
mothers' working, shown in the first column of
Table 4, also shows strong, statistically significant
positive effects of non-family living on acceptance
of employment of married mothers with young
children. A young woman who lived away from
home all of the possible years between age 17 and
marriage, or Time 2, increased her score on this
scale by about 1 point on a 13-point scale
compared with someone who never lived away.
We find similar patterns in our analysis of the total
number of children expected by young women.
Living away from home reduces fertility expecta-
tions, with a decline for those who experience
non-family living throughout the interval of about
a quarter of a child, compared with those who
either always lived with parents or moved straight
from parents to husband. '0
Ideal family size (Table 4, column 4), in
contrast, shows no effect of non-family living.
This result reinforces the theoretical and analytic
differences between these measures. Ideals seem
quite stable, as reflected by the somewhat larger
effect of the prior measure for this than for birth
expectations, and by the lack of effect from all the
new experiences except school enrollment.
The right-most columns of Table 4 present the
two sex-role attitudes scores (Family and Jobs),
measured in 1978. The results show that non-
family living increases both young women's
acceptance of non-family roles for women with
family responsibilities (Family) and their view of
the benefits of women's employment to their
self-esteem and to their families' economic posi-
tion (Jobs). When we analyze these two scales as
measured in 1972, without a Time 1 control, we
find an even stronger effect of non-family living on
Family, but no effect on Jobs (results not shown).
These results for 1978, an outcome measured at the
latest survey year and at the oldest ages, suggest
that the effects of non-family living are not
necessarily short-lived, despite the attenuation
apparent on active work plans; its influence
persists up to a decade for fundamental attitudes
about women's work and family roles.
We performed several checks on the susceptibil-
ity of our findings to changes in the measurement
of non-family living. First, we re-estimated all the
9 We were concerned with the possibility that the
effects we observed for non-family living might be
spurious, resulting from the unmeasured effects of work
experience, since our models include only current
employment status. We thought this unlikely, since
Spitze (1978) found that holding a job rather than going
to college during early adulthood caused a decrease in
young women's taste for employment at age 35. We also
knew that research on the relationship of employment and
non-family living early in adulthood has shown them to
be only weakly related. Many young adults leave home
for non-work related reasons, and many others remain at
home and work after finishing school. McElroy (1983)
found a weak positive relationship between employment
and non-family living for a sample of high school
dropouts and Goldscheider and DaVanzo (1985) found a
weak negative relationship over the seven years after
completing high school in a sample that was restricted to
those who reached twelfth grade.
Nevertheless, reasoning that the problem should be
most acute for employment-related attitudes, we re-
estimated the models of plans for work at age 35 (shown
in Table 3) three times, substituting various detailed
measures of employment history for current employment.
These measures were: (1) the proportion of years since
age 17 that the respondent worked at all at any time
during the year; (2) the proportion of years that the
respondent worked at least 1000 hours (approximately half
time); and (3) the proportion of years that the respondent
worked at least 26 weeks (approximately a half-year).
Each of these models showed exactly the same pattern of
effects of non-family living on changes in work plans,
with the same pattern of significance. In fact, the
coefficients for our measure of non-family living were
larger in each of the alternate specifications than in that
with current employment. We conclude that the use of
current employment does not mask effects of employ-
ment history in the model that theoretically should have
the strongest effects of employment on the outcome
measure, and that our results with current employment
are probably somewhat conservative. To keep the
complexity of the reported results within reasonable
bounds we report only the analyses with current
employment, but the alternative specifications are
available from the authors on request.
10 As we noted earlier, we repeated all these analyses
with this scale coded into a Guttman scale, coded from 0,
for those who agreed that mothers should work under
none of the stated conditions, to 3, for those who agreed
that mothers could work under all the conditions. The
substantive conclusions were identical.
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548 AMERCANSOCOLOGCAL REVEW
Table 3. Effects of Non-family Living and Other Variables on Young Women's Plans to Work at Age 35
Age
xpantoryVrabes 20 22 24
nfamyLvng0101** 0083 0042
Wrk pans for 35 measured at age 17 0279** 0213** 0179**
Back0138**0128**0021
nntact 0075**-0051 0116**
arens Education-0004 0006 -0003
moyd0042 -00330158**
nroed0284**0186**0132*
Sze 00020010-0002
Souh0053*00510057*
Yar-0037**-00070021*
rred-00030031 -0066
vorced/Separated 0023 0049 -0069
mrred-0031 0111 0065
Husbands Total ncom -0006 -0011 0001
Kd 0080*00570161**
moyd*Kd0091 0068 -0079
Educational Attainmnt 0037**0059**0039**
227740928
2 - log-likelihood ratio (df= 18) 240.43 113.93 103.01
One-tailed significance:
* p. 05
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NONAMLYLVNG549
Second, we re-estimated these models using a
specification of non-family living that allows for
separate effects for each number of years of
independent living, given years at risk. It also
controls for number of years at risk, that is, the
number of years between age 17 and the measure
of the dependent variable. In no case did this
fully saturated model significantly improve on the
fit of the restricted model that we estimated, as
measured by F-statistics for the regressions and
Chi-squared statistics for the logits (all p > .08).
Among the control variables, a result worth
noting is that for NONINTACT, which also
measures non-traditional living arrangements.
NONINTACT shows a positive effect on plans for
work at age 35 at two of the three ages presented in
Table 3; in the equations for the other measures
NONINTACT tends to operate in the same
direction as non-family living. Where it has any
effect, it decreases family orientation, suggesting
that living in a non-traditional family during
adolescence moves young women away from plans
for family roles later in life. This finding is
consistent with our proposition that experiences in
non-family living during young adulthood erode an
orientation toward traditional family roles.
We also find that education is less associated
with family-oriented attitudes and plans, as is
current employment, but we see effects of marital
status only for sex-role attitudes and expected
family size. Not surprisingly, women who experi-
ence marital disruption have decreased their
expected number of children. Married women and
working mothers hold more liberal views on the
Jobs measure, whereas divorced and remarried
women are more liberal on the Family scale. Black
women seem to hold more positive attitudes
toward work, however this is measured, and to
have a somewhat larger expected and ideal family
size, but do not differ from whites on family-
related sex-role attitudes.
Our second proposition states that non-family
living not only affects personal plans and expecta-
tions, but also influences global ideals, although
less strongly, since individuals are likely to use the
extenuating circumstances in their particular case
to justify deviations from the ideal that they hold,
at least for a while. The results presented in Tables
3 and 4 offer mixed support for this reasoning. We
find no significant effect of non-family living on
ideal family size. However, we see significant
effects of living away on attitudes toward mothers'
working and both the Family and Jobs dimensions
of the Sex-role attitudes measure. All these
represent global, rather than personal views. We
conclude that non-family living affects some but
not all dimensions of global attitudes.
Our third hypothesis deals with sex differences
in the effects of independent living. The NLS data
contain very few measures of young men's
attitudes toward family life or appropriate roles for
men and women. The one measure available (for
1971 and 1976) corresponds exactly to one of the
scales analyzed for young women: attitude toward
mothers' working. This is shown in the second
column of Table 4. We see no significant effect of
non-family living on men's views, in contrast to
those we found for women. Note, however, that
the coefficient for young men has the expected sign
and is nearly significant at the p
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550AMERCANSOCOLOGCAL REVEW
Table 5. Transformed Logit Coefficients for Models of Young Women's Plans, Attitudes and Expectations
(Controlling for All Variables in Table 2)
Plans for Work at Age 35
202224
Model 1
nfamyLvng0101** 0083 0042
Model 2
oege * awy0173** 0215** 0148**
oege * hom 0118** 0107** 0046
oege other awy0161* 0131 0139*
ncoege awy0000 0007 -0014
Model 3
oege * awy0140** 0078 0026
oege * hom 0088** 0003 -0047
oege other awy0141 0052 0079
ncoege awy0002 0023 0003
Educational attainmnt 0029**0056**0041*
titude towrd Sex-roe
Mothers Wrkng Expected Ideal Attitudes
Girs Boys Famly Size Famly Sizes Famly Jobs
1972 1976 197319731978 1978
Model 1
Nonfamly Living 0979** 0261 -.225** -.066 0161** 0112*
Model 2
College awy0328*0400*0026 0036 0241**0027
College hom -0145 0016 0038 0076 0115*-0061
College other away -0382 0230 -0307* -0282* 0382** 0099
Non-college away 0.551** -0.077 -0.199** -0.083 0.055 0.043
Model 3
College awy0204 -0342 -00090027 0166**0071
College hom -0235 -0567*0012 00690061 -0030
College other away -0427 -0308 -0322* -0285* 0344** 0121
Non-college away 0581** -0089 - 0193** -0081 0067 0036
Educational attainment 0094* 0204** 0020 0005 0024* -0014
models, of a measure of educational attainment.
The two sets of analyses point to the same
conclusion: young women who live away from
home while attending college are more likely to
change their work plans than those who attend
college while living at home. These women, in
turn, are significantly more likely to change their
work plans toward employment than those who
remain at home and do not go to college. Those
who live at home while in college, but live
independently at some other time, also exhibit an
increased preference for working at age 35,
although the effect is not significant. Those who
live away from home without attending college
show no difference from the omitted category.
Adding educational attainment to the model
controls for the effect of years of school completed
by the age in question. This differentiates between
young women who attended college only briefly
and those who completed more years of higher
education. This control attenuates but does not
eliminate the effects of the joint events. The
coefficients suggest that living independently
reinforces the lessons learned at college, pointing
to the socializing effect of time spent with other
students outside the classroom, away from parental
control and influence.
The other panels of Table 5 show the joint
measures of college-going and non-family living
described above for the other outcome measures.
These coefficients suggest that both college
attendance and non-family living affect the magni-
tude of attitude change, whether or not these occur
together. These patterns are not always fully
consistent; in general, however, both those who
lived at home while attending college and then
lived away (a relatively small group), and those
who lived away at college showed more change
than others on the Family factor analysis scores.
As before, adding educational attainment attenu-
ates but does not eliminate these relationships.
The final hypothesis is related to the importance
of including a Time 1 control measuring a given
attitude prior to any experience of non-family
living. One could argue that the relationship we
observe between attitudes and plans and non-
family living arises because those who grew up
with the most non-familial views may be more
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ONAMLYLVNG55
Table 6. Effects of Non-Family Living on Attitudes and Expectations About Family Roles at Time 2 With
and Without the Inclusion of a Baseline Measure
Work Plans for Age 35
ge 20 Age 22 Age 24
Wthout Tm I 110** 120 068
WthTm 1 101** 083 042
Attitudes toward Famly Size Sex-Role Attitudes
Mothers' Working Expected Ideal Family Jobs
Wthout Tm 1 .995**-.211 - .084 .192**.114
WthTm 1 .979**-.225**-.066 .161**.112*
likely than others to live away from home. This
potential problem arises for all analyses where the
initial attitude measure may have occurred after
some experience with non-family living, as is the
case with sex-role scores. If so, the relationship
between non-family living and non-familial atti-
tudes that we observe could be spurious and only
reflect this relationship with the omitted variable.
Our controls for early attitudes, measured prior to
any non-family living, eliminate this possibility for
those outcomes for which we have this baseline;
these are work plans for age 35 and attitudes
toward mothers' working for young women. Both
of these models show the hypothesized effect,
providing strong tests of our central proposition.
These models also allow us to determine the extent
of the strength of the association between non-
family living and early attitudes, and hence, the
likely extent of specification bias in the analyses
without Time 1 controls.
To test our reasoning, we re-estimated all the
young women's models in Tables 3 and 4,
eliminating the initial measure of the dependent
variable. The resulting coefficients for non-family
living are presented in Table 6. Comparison with
the coefficients for non-family living in Tables 3
and 4 shows that adding or deleting the initial
measure makes little difference in the conclusions;
generally the results for non-family living without
controls for the initial measure are slightly stronger
than those with controls, but these differences are
quite small. In only one case, expected family size,
does adding or deleting the initial measure change
the significance of non-family living. Given the
strong relationships between the initial measure
and the later one shown in Tables 3 and 4, it is
clear that including the initial measure improves
the overall fit of the model; however, it does not
eliminate the effects of non-family living.
As a second test of this hypothesis, regression
models were estimated with the non-family living
measure at Time 2 as the dependent variable and
the Time 1 attitudes or work plans variable
included as an explanatory variable. All other
explanatory variables were retained as measured at
Time 2, which allowed us to isolate the effect the
attitudinal measure alone has on the propensity to
live away from home.'3 These results, in Table 7,
show that only the initial work plans variable has a
significant effect on the subsequent propensity for
non-family living-and only for age 22 or later.
The other attitude scales had no effect on
non-family living. These results corroborate those
in Table 6 that show that the percentage change in
the non-family living coefficient is relatively
small, except for the models for work plans at age
22 and age 24, where the coefficients increase 45
to 62 percent when the Time 1 baseline measure is
omitted.
These results provide strong support for our
hypothesis that living away during young adult-
hood is not highly selective with respect to initial
attitudes regarding values or belief systems. Those
with the least family-oriented views to begin with
are not substantially more or less likely to live
away from their parents during the transition to
adulthood, so that these and other analysis of the
effects of non-family living on attitudes and
behavior should not be unduly concerned about
issues of selectivity. However, there is indication
that some selectivity may exist with respect to
expressions of intentions or plans, if these plans
may produce actions that affect living arrange-
ments. In our analysis, specific work plans for age
35 might well be expected to interact with living
arrangements more than judgments regarding
appropriate familial sex roles. In this case, it is
prudent to include a baseline measure, which we
have done in this analysis.
DISCUSSION
We argued earlier in this paper that living away
from home prior to marriage changes young adults'
attitudes, expectations, and plans away from
13 For example, measuring marital status at age 20 in
the work plans model adjusts for the effect marriage had
on the proportion of years lived away from home between
age 17 and 20. If explanatory variables were measured at
Time 1 when all women were single, the effects of the
attitudinal measure would be confounded with the effects
of marriage on the non-family living variable.
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52 AMRCANSOCOLOGCA REVEW
Table 7. Effects of Time 1 Measure on Non-Family
Living Variable at Time 2
me 1 Masure Coefficient Tme 2
Wrk Plans-age 17 .017 age 20
Wrk Plans-age 17 .052** age 22
Wrk Plans-age 17 .090** age 24
Attitudes, Mothers
Workng 1968 0011972
Sex-role Attitudes,
Famly 1972 008 1978
Sex-role Attitudes,
Jobs, 1972 001 1978
family and toward individual concerns. Our results
support this hypothesis consistently, indicating that
young women who lived independently became
more likely to plan for employment, lowered their
expected family size, became more accepting of
employment of mothers, and became more non-
traditional on sex roles in the family than those
who lived with their parents. We found much
weaker effects of non-family living in the tests we
could perform for young men. Our results suggest
that personal plans and expectations respond in the
expected way to experiences in non-family living,
but that some dimensions of ideals and global
attitudes change as a result of this experience, as
well. We also find evidence that living away from
home reinforces the effects of attending college on
young women's attitudes, expectations and plans.
Given these results, it is important to learn more
about why non-family living should have such an
effect on attitudes about new family formation and
the kinds of families likely to be formed. We
suggest the following possibilities. First, living
away from home lessens parental control over their
children's activities and may weaken the link
between parents' values, attitudes, and behavior
and those of their children. Young adults in their
own apartment are freed from parental curfews and
supervision of their friends and behavior, can
manage their own household in the way that they
choose, and may have a sexual freedom impossible
in their parents' house. Second, experience in
independent non-family living may equip young
adults with new social and domestic skills (such as
housekeeping, maintenance of a dwelling unit or
car, household finance, health care, and entertain-
ing). Living away from home may give both young
men and women the self-confidence that they can
get along without a family and may enable them to
acquire the skills that they need to maintain their
independence as long as they wish. Third,
non-family living potentially exposes young adults
to a wider variety of experiences and influences
than those encountered while they live with their
parents. These may cause individuals to change
their plans and expectations for themselves, and
their views of appropriate behavior for men and
women, in general. We do not test any of these
possible mechanisms directly, but our results
suggest that such tests might prove a fruitful
avenue for further research.
Previous research on the development and
revision of sex-role attitudes has focused on
education, employment (Spitze, 1978; Dambrot et
al., 1983; Morgan and Walker, 1983), marriage,
becoming a parent, and divorce (Spitze and Waite,
1981). We find that education and employment are
associated with less family-oriented attitudes and
plans, but we see effects of current marital status
primarily for sex-role attitudes. Married women
hold less traditional views on the economic
benefits to the family of women's employment,
and divorced women and working mothers are
more liberal on the appropriate division of roles
within the family. Non-family living, by contrast,
seems to have broader effects than marital status,
with coefficients sometimes larger than those of
employment and education. Non-family living is a
previously ignored but potentially important expe-
rience in the transition to adulthood, especially as
it influences young adults' attitudes and plans for
their own lives.
One particularly significant result of this re-
search is the finding that the omission of Time 1
controls has little effect on measuring the impact of
non-family living on later orientations toward work
and family life. This provides increased confidence
that results obtained previously that show the
impact of non-family living on the likelihood of
marriage were not biased by the omission of some
underlying anti-family attitude among those who
both live away from parents early in adulthood and
are also unlikely to marry. It also opens the way to
research on other possible sequelae of non-family
residence in early adulthood, such as marital
dissolution, or less traditional assignments of tasks
within marriage, allowing greater range in the
analysis of the forces leading to change in marriage
and the family in the late twentieth century.
These changes in the nature of the family, many
of which we discussed earlier, have altered some
of the bases on which traditional, gender-based
divisions of labor rested. These divisions may have
served some important functions under earlier
conditions (Marwell, 1975). But as Marini (1984)
has argued, norms about the transition to adulthood
tend to reflect behavior, as well as affect it, and
thus may change as behavior changes. The shifts in
individual attitudes, plans, and expectations that
our findings link with experiences with non-family
living may be a first step in the process of
alteration of norms. Thus, our finding that
non-family living influenced all our measures of
behavioral plans and evaluations, but did not affect
some indicators of global ideals, should not be
interpreted as showing that non-family living may
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NONAMLYLVNG553
only have a transient effect, one with impacts only
on those experiencing it. For if Marini is correct,
the increase in non-family living, by changing
plans relating to male and female roles in the
family, may presage larger shifts than we have
already observed in norms about family life.
APPENDIX
Attitudes towards mothers' working
Now I'd like you to think about a family where there is
a mother, a father who works full-time, and several
children under school age. A trusted relative who can
care for the children lives nearby. In this family situation,
how do you feel about the mother taking a full-time job
outside the home-
a. If it is absolutely necessary to make ends meet?
b. If she wants to and her husband agrees?
c. If she prefers to work, but her husband doesn't
particularly like it?
Sex-role attitudes scores #1 and #2, 1972
a. Modern conveniences permit a wife to work
without neglecting her family.
b. A woman's place is in the home, not in the office
or shop.
c. A job provides a wife with interesting outside
contacts.
d. wife who carries out her full family responsibilities
doesn't have time for outside employment.
e. A working wife feels more useful than one who
doesn't hold a job.
f. The employment of wives leads to more juvenile
delinquency.
g. Working wives help to raise the general standard of
living.
h. Working wives lose interest in their home and
families.
i. Employment of both parents is necessary to keep up
with the high cost of living.
Sex-role attitudes scores #1 and #2, 1978
The 1978 series includes items a, b, d, e, f, and i. It also
includes the questions listed below.
j. It is much better for everyone concerned if the man
is the achiever outside the home and the woman
takes care of the home and family.
k. Men should share the work around the house with
women, such as doing dishes, cleaning, and so
forth.
1. A working mother can establish just as warm and
secure a relationship with her child as a woman who
doesn't work.
m. Women are much happier if they stay at home and
take care of their children.
n. A woman should not let bearing and rearing
children stand in the way of a career if she wants it.
Items a and c had no relationship with either dimension in
the 1972 scales, and were dropped; items a and k were
deleted from the 1978 scores for the same reason. Items
e, g and i loaded highly on score #2 (jobs), and the
remaining items loaded highly on score #1 (family).
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