AMERICAN JOURNAL OF HUMAN BIOLOGY 15:667–680 (2003)
Timing Is Everything: A Reconsideration of Fetal Growth
Velocity Patterns Identifies the Importance of Individual
and Sex Differences
MICHELLE LAMPL1* AND PHILIPPE JEANTY2
1
Department of Anthropology, Emory University, Atlanta, Georgia
2
Women’s Health Alliance, Nashville, Tennessee
ABSTRACT
Fetal growth has been posited to follow a ‘‘timing hypothesis’’ sequence in which
the second trimester favors a single growth velocity peak in body length and the third trimester
accommodates a single growth velocity peak in weight accrual. To our knowledge, this proposition
has never been tested with high-frequency longitudinal ultrasound data from normally growing
human fetuses. The present study examined whether fetal growth in leg length had its peak
velocity at or about 20–26 gestational weeks and declined subsequently and whether estimated
fetal weight velocity was maximal at or about 33 weeks and declined subsequently; if the greatest
acquisition of leg length occurred in the second trimester and weight in the third trimester; and if
birth outcomes reflected these relationships. The data in this study included approximately
weekly longitudinal ultrasound data collected from 44 maternal/fetal pairs in Brussels,
Belgium. Diaphyseal lengths of the femur and tibia provided information on leg growth and
estimated fetal weight was assessed from the biparietal and occipital-frontal head diameters
and transverse and anterior–posterior diameters of the abdomen. Growth patterns were investigated from individual growth curves derived from daily growth velocity z-scores. Paired t-tests
compared individuals’ trimestral increments in leg length and fetal weight. Least-squares regression models employing the robust procedure for repeated measurements were used to test for
relationships between trimester, size, growth rates, and birth outcome, controlling for day of
measurement, sex, maternal smoking, and gestational age at birth. The normal fetuses in this
study grew by pulsatile patterns of leg and estimated weight acquisition, not a single peak and
decline process. Greater incremental growth in estimated fetal weight occurred during the second
trimester and leg length in the third trimester. Individual and sex effects were significant in
growth velocity patterns. Girls grew with greater synchrony between leg and weight growth and
were accelerated by comparison with boys, with faster leg growth predicting lower ponderal index
by the second trimester. Birth outcomes were sex-specific in timing effects and predictive variables. These results support the importance of sex-specific analyses, reemphasize the common
notion that girls grow faster than boys, and direct attention to cross-talk between energy
# 2003 Wiley-Liss, Inc.
resources and growth. Am. J. Hum. Biol. 15:667–680, 2003.
Common assumptions regarding the timing of fetal growth in body dimensions posit
that the primary time for growth in body
length and weight are sequential, with the
second trimester focused on length and the
third trimester devoted to fetal weight gain.
This notion was formalized in 1982 as the
‘‘timing hypothesis,’’ presented as an interpretive schema for understanding causal
relationships between prenatal insult and
neonatal body size and proportion (Villar
and Belizan, 1982). This model proposed
that a better understanding of intrauterine
growth retardation follows from an appreciation of developmental timing. Specifically, it
was suggested that neonatal size and body
proportions could themselves provide clues
as to when in fetal development a growth
ß 2003 Wiley-Liss, Inc.
insult had occurred. First trimester insults
were said to produce proportionately small
neonates, second trimester insults resulted
in short neonates, and third trimester
insults were assumed to produce long and
thin neonates. The evidentiary base cited to
substantiate the fetal growth timing propositions were two graphs originally published
by Tanner (1978), illustrating a peak in
fetal growth in crown–heel length at about
*Correspondence to: M. Lampl, 1557 Pierce Drive,
Department of Anthropology, Emory University, Atlanta,
GA 30322. E-mail: mlampl@emory.edu
Received 4 March 2003; Accepted 5 May 2003
Published online in Wiley InterScience (www.interscience.
wiley.com). DOI: 10.1002/ajhb.10204
668
M. LAMPL AND P. JEANTY
20 gestational weeks of age and a peak in
growth in fetal weight at about 33–34
weeks, followed by a decline. These illustrative images of fetal growth rate are reproduced in Figure 1.
The timing hypothesis assumptions have
been questioned several times by empirical
data: In a study with approximately monthly
ultrasound assessments from 17 weeks, no
distinctive growth patterns in femur length
(used as a proxy for body length) or abdominal diameter/circumference (used as a proxy
for fetal weight) were found by trimester,
and it was concluded that growth retardation in both symmetrical (body and head
proportionately reduced) and asymmetrical
(body reduced proportionately greater than
head circumference) intrauterine growth
retardation (IUGR) started in the second
trimester (Vik et al., 1997). Larger studies
previously concluded that body proportions
Permission to reproduce this figure
electronically was not obtained from
the original publisher
Fig. 1. Fetal growth velocity in crown–heel length
(above) and body weight (below) as per Tanner (1978,
1990). Reprinted by permission of the publisher from
FETUS INTO MAN: PHYSICAL GROWTH FROM
CONCEPTION TO MATURITY by J. M. Tanner,
pp. 39, 41, Cambridge, Mass.: Harvard University Press,
Copyright # 1978, 1989, by J. M. Tanner.
at birth and growth retardation do not meet
the timing hypothesis expectations as outlined above (Kramer et al., 1989) and are
not informative about prenatal growth rate
(Petersen et al., 1992).
Investigations of the timing effects of
maternal weight gain and risk for IUGR
have resulted in conflicting reports, with
some samples documenting that both trimesters carry risk for IUGR (Strauss and Dietz,
1999) and others identifying the second trimester as the most important for maternal
weight gain effects (Abrams and Selvin,
1995), with some data more specifically suggesting a threshold effect in early to midpregnancy for birth outcome (Stein et al.,
1995). Ecologically oriented studies have
concluded that it is the third trimester that
is most significant and body length is the
variable most affected (Neufeld et al.,
1999b).
In spite of these critical inquiries, the timing hypothesis paradigm persists and is central to clinical interpretations and public
health interventions aimed not only at fetal
growth and well being, but postnatal growth
and health as well (Barker et al., 1989). The
fetal growth timing assumptions are part of
a considerable theoretical debate focusing
on the nature and outcomes of fetal programming, forging a theory of causal links
between the timing of specific prenatal
insults and resulting susceptibility to later
disease by way of birth size and proportions
(Barker et al., 1993; Law et al., 1992).
Thus, it is of some interest to reconsider
the evidentiary base of the timing hypothesis
paradigm. An examination of the data
sources giving rise to the graphs in Figure 1
is informative. The curve of growth velocity
in crown–heel length is based on unpublished data from ‘‘several sources’’ (Tanner,
1990:39), and according to the author, the
peak velocity may be up to 6 weeks later
than shown, or between 20 and 26 gestational weeks.
Birthweights of live-born premature male
infants are cited as the basis for the graph
describing a 33–34 week peak in fetal weight
growth velocity (Tanner, 1990:41). The
accompanying text notes that these graphs
should not be taken to represent individual
growth patterns, but serve only to describe
the patterns of fetal growth in general. It
should be noted that these general patterns
derive from growth velocities calculated
monthly for length and annually for weight.
669
FETAL GROWTH PATTERNS
In spite of the careful caveats of the original author, the messages taken from the
graphs have become the basis for both clinical
interpretation and research rationale about
fetal growth and development in individuals.
To our knowledge, the explicit propositions of
the timing hypothesis have not been previously tested with longitudinal fetal growth
data collected with sufficient frequency to
identify the details of growth velocity changes
in normally growing fetuses.
The present study employs serial fetal
ultrasounds and investigates three aspects
of the timing hypothesis paradigm: The
patterns of fetal length and weight growth
velocity in the individual, the temporal
relationships between the two body parameter velocities, and the predictability of
birth outcome. The first proposition tested
is that fetal growth in body length has its
peak velocity in the second trimester, at or
about 20–26 gestational weeks (Tanner,
1978, 1990), and declines subsequently.
This specific statement is not without contest in its original form. Longitudinal study
of crown–heel length measurements are not
possible throughout pregnancy due to the
biological constraints on the position of the
fetus, characterized by spinal curvature and
limb flexion. Crown–rump measurements
are, likewise, not highly accurate in a longitudinal study of the late-developing fetus
due to poor positional replicability. Because
of these limitations, the present investigation employed growth of the leg to assess
growth in length. The variable ‘‘leg length’’
was the sum of individual diaphyseal measurements of the tibia and femur. Statistical
analysis suggested that this parameter was
useful: Weekly growth rates of the tibia and
femur were significantly correlated across
the sample (P < 0.01, pairwise with
Bonferroni correction). Thus, leg growth
velocity was used as a reasonable proxy
for total body length growth velocity, in lieu
of the unobtainable crown–heel length or
unreliable measurement of crown–rump length
to test the timing hypothesis propositions
regarding fetal ‘‘growth in length.’’ The present approach is explicitly an approximation
and cannot account for crown–rump growth
rates and resulting upper to lower body
proportionality contributions to total body
length. None of these issues were addressed
in the originally published propositions and
are not commonly noted when employing the
timing hypothesis assumptions.
The investigation of the growth patterns
of the fetal leg has merit in the context of
recent reports of associations between fetal
leg growth and childhood health outcomes.
For example, third trimester femur length
has been found to predict well childhood
height (Cacciari et al., 2000) and fetal
femur length, and growth rate between 18
and 38 weeks has been found to be inversely
associated with childhood blood pressure
(Blake et al., 2002). Moreover, strong predictive relationships have been identified
between birth length and adult height
(Sorensen et al., 1999), and the risk of coronary heart disease has been inversely
related to leg length but poorly associated
with trunk length in adults (Smith et al.,
2001). Thus, the growth patterns of the
fetal leg may have long-term implications.
The second specific proposition addressed
in the present study is that fetal weight velocity is maximal at or about 33–34 gestational
weeks of age and declines subsequently
(Tanner 1978, 1990). A corollary to the first
two propositions is that a trimestral sequence
occurs, such that the greatest growth rate
and acquisition of length is during the second
trimester, and the greatest growth rate and
acquisition of weight is during the third trimester. This inference is also examined.
Finally, the predictions that maximal effects
of length and weight growth on birth outcome occur during the second and third
trimesters, respectively, are explored in the
growth patterns of this sample.
SUBJECTS AND METHODS
Sample
Forty-four maternal/fetal pairs were participants in a longitudinal growth study
between the ages of 13 weeks and birth,
with a protocol designed to obtain weekly
measurements. All participants were employees at the same health care institution in
Brussels, Belgium, and volunteered under
conditions of informed consent. Gestational
ages were determined as the time from last
menstrual period confirmed by measurements of crown–rump length between 8–10
weeks. All pregnancies were single births
of healthy mothers with uncomplicated
pregnancies. Thirty-three subjects had birth
data on weight, length, and infant sex (52%
males).
670
M. LAMPL AND P. JEANTY
Ultrasound measurements and rationale
Six measurements taken serially on each
fetus contributed to the present analysis: the
biparietal diameter (BPD) and occipitalfrontal diameter (OCF) of the head, the
transverse and anteroposterior diameters of
the abdomen (TAD, APAD), and the diaphyseal lengths of the two bones of the lower leg,
the tibia, and femur. These measurements
were obtained by a physician (Jeanty) using
calipers and a Toshiba SAL 10A with a frame
freeze and a 2.4 MHz transducer. Detailed
descriptions of the measurement protocol
have been previously published (Jeanty et
al., 1982, 1984b,c).
Estimations of fetal weight were a calculated composite of individual body measurements. In this study, the previously
validated and published equation is used
(Jeanty et al., 1984a) where estimated fetal
weight (EFW) ¼
Log ½ð0:34 BPÞ þ ð2:7 OCFÞ ðTADÞ
þð2 APADÞ=100
This formula was chosen because it does not
rely on leg measurements, but derives from
the two dimensions of the head and abdomen. The choice of this composite estimation
permits unconfounded comparison between
estimated fetal weight and leg growth.
Analysis methods
The object of this study was to identify the
patterns and timing of fetal growth velocity in
leg length and fetal weight at the level of the
individual. Growth velocities were calculated
in terms of change per day to accommodate
unequal measurement intervals, as no subject
met the weekly protocol for the duration of
the study precisely each seventh day. The
equality of distributions across subject, week,
and trimester was investigated (ANOVA,
Kruskall-Wallis). Both sample and individual
z-scores were calculated for the growth velocities in leg and fetal weight in order to track
individual velocity changes and to provide a
basis for comparing the growth patterns of
the two variables, measured by different
scales. All analyses comparing growth rates
between variables are based on standard
scores. Cubic splines were employed to construct individual growth curves.
Least-squares regression models employing
the robust procedure for repeated measure-
ments were used to test for age-specific and
trimestral effects on leg and EFW growth
velocities. Individuals’ incremental growth
in leg length and estimated fetal weight was
derived across the second (weeks 13–26) and
third (weeks 26–38) trimesters from the
growth curves to control for variability in
day of ultrasound measurement. ShapiroWilks test for normality and two-tailed t-test
procedures investigated the equality of means
across trimesters (paired t-test for unequal
variance). The effects of sex and maternal
smoking on incremental growth were investigated by least-squares regression.
Least-squares regression models employing the robust procedure for repeated measurements were used to explore trimestral
relationships in size, growth rates, and
birth outcome. Gestational age at birth was
included in all regression models investigating birth outcomes. All statistical analyses
were based on the computational assumptions of Stata 6 (Stata Corp., Release 6.0.
College Station, TX) and significance was
accepted at P 0.05.
RESULTS
Fetal size in terms of mean femur length,
biparietal, and abdominal diameters were
between the 40th and 60th centiles of reference standards for other similar European
samples across the second and third trimesters (Crequat et al., 2000; Guihard-Costa
and Larroche, 1995). The means (and standard deviations, SD) for birthweight and
length were 3,349 g (SD 399 g) and 50.4 cm
(SD 1.5 cm), respectively. All births were
term, with an average gestational age of
275 days (39.2 weeks, SD 7.4 days) and
there was no intrauterine growth retardation assessed by weight for gestational age.
All subjects received pediatric care at birth
and all neonates were clinically normal.
Controlling for day of ultrasound measurement and maternal smoking, significant
sex differences were found in terms of leg
length, with girls exceeding boys by midsecond trimester (beta 3.1, P ¼ 0.06, model
R2 ¼ 0.77, P ¼ 0.00). No significant sex
differences were found in leg length and
EFW in the third trimester.
Fetal growth velocity patterns
The distributions of growth velocities for
estimated fetal weight and leg length by
FETAL GROWTH PATTERNS
Fig. 2. Distribution of growth velocities for estimated
fetal weight (above) and leg length (below) by gestational
weeks of age. Pooled data are shown as means (horizontal lines within boxes), the interquartile range (boxes),
and the 95% range (bars). Within individuals, the velocities are normally distributed. The pooled sample’s
ranges result from the pattern differences between children: each vertical range includes both peaks and
troughs of individual subjects.
gestational week of age are plotted in Figure 2.
Significantly different distributions characterized both variables by week (P < 0.01)
and EFW velocity by trimester (P < 0.01).
Thus, pooling the data was inappropriate
and individual-level analyses were undertaken to address the research question
regarding the nature of individual growth
velocity patterns.
Neither the growth velocity of the leg nor
that for estimated fetal weight was characterized by a single peak value followed by
decline. Instead, the growth patterns of
both variables followed a pulsatile pattern
of peaks and troughs (Fig. 3), unassociated
with the timing hypothesis peak ages (Fig. 4).
The significant variance heterogeneity by
week found in the pooled data reflected individual differences in the timing of the peaks
and troughs. Combining individual growth
671
Fig. 3. Growth velocity in the leg (above) and estimated fetal weight (below) in an individual fetus (subject
number 6). The leg growth velocity graph provides an
overlay of diaphyseal length velocities of the tibia (circles) and femur (triangles), together with the calculated
leg length velocity (squares). The y-axis is mm/day to
correct for unequal measurement intervals actualized
under the weekly protocol. The y-axis for the growth
velocity of estimated fetal weight is grams per day.
patterns would have superimposed one individual’s growth peak pulse on another’s
trough and attenuated the pulsatile patterns
by which the individuals grew. These data
emphasize the importance of individual differences in growth patterns in fetal development.
Fetal leg and weight growth relationships
As no single-peak growth pattern characterized the growth velocities of either leg
length or EFW in these individuals, other
approaches were further explored to understand the relationship of the present sample’s growth to the timing paradigm. Were
there some broader patterns associated with
individuals’ growth velocities in leg length
and EFW that might be compatible with
the generalizations presented in Figure 1?
The first approach tested the proposition
that comparatively high velocities over the
672
M. LAMPL AND P. JEANTY
Fig. 4. The multiple peaks and troughs by which
individual growth in leg length (circles) and estimated
fetal weight (triangles) velocity progressed is illustrated
(Subject 7). The pattern of multiple peaks contrasts with
the predicted fetal growth model in terms of overall single peak and decline process and timing.
range of the respective predicted peak
growth periods might have occurred. Leastsquares regression for repeated measurements investigated this by comparing the
leg growth velocities during the putative
timing hypothesis peak length growth interval (20–26 weeks’ gestational age) with all
other weeks. The model controlled for potential confounding effects of day of measurement, maternal smoking, and sex, and was
run separately for both raw velocities and
velocity standard scores. No significant
effects of ‘‘peak growth period’’ were identified (model P ¼ 0.00, R2 ¼ 0.08) in leg length
growth velocity. Likewise, the growth velocities of EFW during weeks 33–34 were compared to all other weeks, controlling for the
same potential confounders. A significant
negative slope was identified for the EFW
growth velocity during these weeks (beta of
–0.43 for EFW velocity standard score, SE
0.12, range –0.66 to –0.19, model P ¼ 0.00,
R2 ¼ 0.32).
Least-squares regression for repeated
measurements also investigated the effects
of trimester (second vs. third) on individuals’
leg length and EFW growth velocities (separately for both raw velocities and z-scores),
controlling for confounders. No significant
linear effects of trimester were found for
either leg velocity (model P ¼ 0.00, R2 ¼
0.07) or EFW velocity (model P ¼ 0.00,
R2 ¼ 0.24). Thus, the pooled sample data did
not identify significant effects of either the
timing hypothesis peak growth weeks or the
associated trimesters on leg length or fetal
weight growth velocities.
Finally, individuals’ incremental growth
in each trimester was assessed to investigate
the proposition that greater growth in length
occurs during the second trimester and
greater growth in fetal weight during the
third trimester. Increments were derived
from individuals’ leg length and EFW
growth curves to identify growth progress
in the second trimester (between weeks
13–26) and third trimester (weeks 26–38).
Total EFW incremental growth in individuals was significantly greater in the second
trimester than incremental growth in leg
length (t-tests, P < 0.00). This was followed
by greater growth in leg length by comparison with EFW in the third trimester (t-tests,
P ¼ 0.00) (Fig. 5). No significant effects of
sex or maternal smoking were evident in
comparisons investigating equivalence of
means. However, least-squares regression
identified significant negative effects of
maternal smoking on individuals’ leg length
increments during the third trimester,
controlling for sex (beta coefficient, –0.34,
SE 0.12, P ¼ 0.01, R2 ¼ 0.24, model P ¼
0.03). On further investigation, there was no
significant effect on females, but maternal
smoking was significantly associated with a
negative slope in leg length increment
during the third trimester for males (beta
coefficient, –0.54; SE 0.17; 95% CI –0.92 to
–0.17; P < 0.01) with an R2 ¼ 0.43 and model
P < 0.01.
These analyses led to the question: ‘‘If
there was not a simple sequential relationship of a single second trimester peak in leg
growth followed by a single third trimester
peak in weight growth, was there another
relationship between the two aspects of
body growth?’’ A comparison of the fetal
weight and leg length velocity growth patterns in individuals identified three relationships. First, there was a pattern of ‘‘copulsatility,’’ when growth pulses in both leg
length and fetal weight velocities occurred
simultaneously. A second relationship was a
‘‘beat frequency pattern,’’ in which one variable pulsed at a multiple of the other. Third,
the leg and weight growth pulses exhibited a
‘‘trade-off growth,’’ when the parameters
were pulsing in opposition.
For example, the subject illustrated in the
top panel of Figure 6 (Subject 32) grew by a
3:2 leg length:EFW pulse pattern between
FETAL GROWTH PATTERNS
673
Fig. 5. Individuals’ incremental growth in EFW was greater than leg length in the second trimester, and
incremental growth in leg length exceeded EFW across the third trimester (t-test for correlated samples, P < 0.01).
Mean incremental standard scores (dots), SE (boxes), and SD (bars) are illustrated.
Fig. 6. Individual growth velocity patterns in leg
length (darker pen, circles) and weight (lighter pen,
squares) for Subjects 32 (female, above) and 31 (male,
below). The growth curves were generated from cubic
splines. The y-axis represents z-score change per day,
and the x-axis is gestational age in weeks. Individuals’
leg length did not proceed by a single peak at 20–26
weeks, followed by decline, and EFW did not grow by a
process with a peak weight velocity about 33 weeks.
18–28 weeks, when the timing shifted to copulsatility. The individual illustrated in the
bottom panel of Figure 5 (Subject 31) grew
by a trade-off pattern throughout gestation.
The top panel was a female and the bottom
panel was a male.
These qualitative patterns were confirmed
by several approaches. First, correlation
analysis identified that females experienced
significant correlations between leg length
and EFW growth velocities in both the
second and third trimesters (pairwise,
Bonferroni correction P ¼ 0.05, 0.01, respectively); males did not.
Controlling for day of ultrasound measurement and the potential confounding
effect of maternal smoking, regression analysis identified the quantitative directional
effects of this relationship for females
(Table 1). In the second trimester, leg length
and EFW growth velocities predicted reciprocal effects that were of roughly similar
magnitude (on the order of 0.2 SDs). In the
third trimester, leg growth velocity predicted
a modest increase in EFW velocity slope,
while EFW effects on leg growth remained
relatively the same. Thus, females experienced coordinated growth velocity patterns
throughout gestation. No significant associations were found for males in growth velocity
between EFW and leg length.
In addition, a sequential temporal relationship in size was identified in which the
EFW during the second trimester (week 23)
modestly predicted leg length during the
third trimester (week 32) for females (beta
0.66, P ¼ 0.06, R2 0.85, model P ¼ 0.02). No
674
M. LAMPL AND P. JEANTY
TABLE 1. Robust regression results by trimester for females’ growth
velocities, controlling for gestational age and maternal smoking
Leg velocity
Beta
SE
t
P
95% Cl
R2, model P
EFW velocity
Females
Trimester 2
Trimester 3
0.24
0.34
0.09
0.07
2.8
4.7
0.01
0.00
0.05, 0.42
0.19, 0.49
0.06, 0.05
0.19, 0.00
EFW velocity
Beta
SE
t
P
95% Cl
R2, model P
Leg velocity
Females
Trimester 2
Trimester 3
0.19
0.50
0.09
0.13
2.1
3.8
0.05
0.00
0.00, 0.38
0.22, 0.78
0.06, 0.01
0.19, 0.00
Analyses employed growth velocities’ standard scores.
TABLE 2. Regression results by trimester for models predicting estimated fetal weight (z-score)
from leg length (z-score) controlling for gestational age, sex, and maternal smoking (total sample)
and gestational age, maternal smoking (by sex)
Fetal weight (z-score)
Trimester 2
Leg length (z-score) (Total sample)
Males
Females
Trimester 3
Leg length (z-score) (Total sample)
Males
Females
Beta
SE
t
P
95% Cl
R2, model P
0.68
0.65
0.73
0.10
0.15
0.15
6.5
4.2
4.9
0.00
0.00
0.00
0.47, 0.89
0.32, 0.97
0.41, 1.04
0.94, 0.0
0.94, 0.0
0.94, 0.0
0.30
0.28
0.24
0.06
0.07
0.10
4.7
4.1
2.3
0.00
0.00
0.04
0.17, 0.43
0.13, 0.42
0.01, 0.46
0.83, 0.0
0.85, 0.0
0.84, 0.0
TABLE 3. Regression results by trimester for models predicting leg length (z-score) from
fetal weight (z-score) controlling for gestational age, sex, and maternal smoking (total sample)
and gestational age, maternal smoking (by sex)
Leg length (z-score)
Trimester 2
EFW (z-score) (Total sample)
Male
Female
Trimester 3
EFW (z-score) (Total sample)
Male
Female
Beta
SE
t
P
95% Cl
R2, model P
0.29
0.26
0.33
0.04
0.05
0.06
7.9
5.2
5.7
0.00
0.00
0.00
0.22, 0.37
0.16, 0.37
0.21, 0.46
0.97, 0.0
0.97, 0.0
0.97, 0.0
0.45
0.60
0.28
0.11
0.19
0.11
3.9
3.2
2.6
0.00
0.01
0.02
0.22, 0.68
0.20, 1.00
0.05, 0.52
0.90, 0.0
0.89, 0.0
0.92, 0.0
significant reverse effects were identified
and no such relationship was found for
males.
The contemporaneous size relationships
between fetal leg length and weight were
also investigated by regression analyses
(Tables 2, 3). Controlling for day of ultrasound measurement and maternal smoking,
the slopes of the regression lines for leg
length on fetal weight were greater during
the second trimester than in the third trimester (approximately two-fold for males, and
three-fold for females). By contrast, for models predicting leg length from EFW, the
slopes of the regression lines doubled for
males in the third trimester by comparison
with the second, while they dropped modestly for females. Thus, leg growth in the
third trimester male was heavily influenced
by third trimester EFW.
675
FETAL GROWTH PATTERNS
attenuated in the third trimester, when the
slope of leg length to birth length outcome
dropped by one-half, after controlling for the
positive effects of EFW and the negative
effects of third trimester leg growth velocity.
Thus, females with long legs in the second
and third trimesters were longer at birth.
However, controlling for these effects, girls
who had high third trimester leg growth
rates were significantly shorter at birth.
No effects were identified in the second
trimester for boys. In the third trimester, a
model with both EFW and leg length best
predicted birth length in boys, with EFW
predicting twice the outcome effects of leg
length.
Predictability of birth outcome
Regression analyses investigated the trimestral effects that leg length and estimated
fetal weight had on predicting birth outcome
in total body weight, length, and ponderal
index (Table 4) controlling for gestational
age at birth, age at ultrasound measurement, and maternal smoking. Significant
sex differences were found in the predictive
relationships between the timing of body
growth and birth outcome.
Birth length. Among girls, leg length in the
second trimester significantly predicted
birth length. This relationship continued
TABLE 4. Birth outcomes predicted by robust regression models controlling for age at ultrasound measurement,
gestational age at birth, and maternal smoking
Birth outcome
Birth length
Trimester 2
Females
Leg length
Trimester 3
Males
EFW
Leg length
Females
Leg length
Leg velocity
EFW
Birth weight
Trimester 2
Males
EFW
Leg length
Trimester 3
Males
EFW
Leg length
Females
Leg length
EFW
Ponderal index
Trimester 2
Males
EFW
Leg length
Females
Leg length
Trimester 3
Males
Leg velocity
Leg length
EFW
Females
Leg velocity
Leg length
EFW
P
95% Cl
R2, model P
2.9
0.02
0.5, 4.1
0.34, 0.03
0.37
0.28
3.2
2.1
0.01
0.06
0.37, 2.0
0.03, 1.2
0.41, 0.00
1.3
0.1
0.9
0.49
0.57
0.04
2.7
2.8
1.7
0.02
0.02
0.12
0.27, 2.4
0.18, 0.02
0.30, 2.2
0.36, 0.03
1.1
1.6
0.3
1.1
3.4
1.5
0.01
0.16
0.4, 1.8
0.7, 3.8
0.40, 0.00
1.8
1.5
0.7
0.8
2.6
2.0
0.02
0.06
0.31, 3.3
0.10, 3.2
0.56, 0.00
2.0
1.8
0.7
0.8
2.8
2.1
0.02
0.06
0.47, 3.5
0.04, 3.6
0.32, 0.01
1.4
1.5
0.7
1.9
2.0
0.8
0.07
0.45
0.1, 2.9
2.6, 5.6
0.39, 0.00
3.8
1.4
2.7
0.02
6.7,
0.20, 0.10
0.2
2.2
0.1
0.1
1.4
1.2
2.1
1.6
0.1
0.05
0.13
0.90
0.4, 0.00
0.7, 5.2
2.5, 2.8
0.46, 0.00
0.2
1.0
2.0
0.1
1.0
1.8
3.1
1.0
1.1
0.01
0.32
0.28
0.05, 0.3
3.2, 1.1
1.8, 5.8
0.08, 0.04
Beta
SE
t
2.3
0.8
1.2
0.6
All variables were transformed to z-scores prior to analysis.
0.76
676
M. LAMPL AND P. JEANTY
Birthweight (BW). No significant relationship was evident for females in the second
trimester, but in the third trimester both leg
length and EFW together best predicted BW.
For males, EFW was the significant factor in
predicting outcome, increasing across trimesters by nearly 60%.
Ponderal index (PI). For females in the second trimester, only leg length in the second
trimester significantly predicted PI at birth,
such that a 1 z-score leg length increase predicted a negative 3.8 z-score change in PI
at birth. Thus, long legs by the second trimester predicted a long and thin female
neonate at birth. Controlling for leg length
and fetal weight, leg growth velocity in the
third trimester positively predicted birth PI.
In boys, EFW in the second trimester modestly positively predicted PI. By the third
trimester, only leg velocity growth rate was
a significant predictor, with negative effects
on PI at birth.
DISCUSSION
Contrary to the commonly cited notion
regarding the pattern of fetal growth, there
was no single peak in growth velocity of
either leg length or estimated fetal weight
in the patterns of individual growth in this
sample. Specifically, leg growth velocity was
not characterized by a single or maximal
peak range between 20 and 26 weeks of
age, followed by declining velocity, and estimated fetal weight growth did not reach a
peak at about 33 weeks of age. These results
are confined to a clarification of the contribution made by leg growth to the timing
hypothesis propositions about total body
length. The growth patterns of both body
parameters in these healthy normally growing fetuses were nonlinear, with multiple
peaks and troughs.
Further, the timing hypothesis proposition that the second trimester is the interval
of greatest length acquisition, followed by
weight in the third trimester, was not supported by the present study. In this sample
the growth patterns were the opposite, with
estimated fetal weight growth accrual
declining after the second trimester and leg
growth in the third trimester continuing
apace with, or exceeding, that of the second.
Regression analyses of within- and
between-term effects identified more com-
plex relationships between growth in fetal
weight and leg length, with significant sex
effects. Growth of legs and fetal weight progressed by a more synchronous pattern in
females than males, and females experienced
earlier growth of lower limbs than boys, suggesting advanced developmental timing.
While second trimester EFW predicted leg
length in third trimester females, third trimester EFW predicted birth length in males:
a similar relationship, offset in timing.
It can by hypothesized that girls are more
canalized, with their birth outcomes set by
genetics and in utero conditions earlier than
boys. This may be influenced by hormonal
conditions as female ovarian development,
peaking in the middle of the second trimester, contributes to growth and maturation.
Whether the postnatally documented effect
of estrogen on bone growth operates prenatally remains to be documented (Okazaki
et al., 2002).
The male delay in growth and development may result in increasing male vulnerability, as their growth is more dependent on
third trimester conditions. Greater daily
fetal weight growth rate in third trimester
males has been previously reported in a
high-risk population (DeJong et al., 1998).
A time of increased strain on maternal
resources in general (Martinez-Morales et
al., 1999), this timing difference may underlie some of the documented sex differences in
male risk during gestation (e.g., Zaren et al.,
2000). This was seen in the present sample
as the negative slopes of leg length increment that were predicted by maternal smoking in the third trimester. Overall, these
results predict that males born prematurely
are at greater risk for consequences of immaturity than females.
This study suggests that size at birth has
different biological meanings for each sex,
reflecting a different developmental timing
program by sex. This is relevant to ongoing
debates about the health sequelae of birth
size in later life (Barker, 1995). Many studies
find the epidemiological relationships
between low BW and/or low PI apply only
to males (Kuzawa, 2001; Suzuki et al.,
2000; Valdez et al., 1994; Ziegler et al.,
2000). This makes sense if the relationships
found here apply more generally.
For example, in this sample low PI at birth
accompanied a fast-growth pattern in girls,
as those with longer legs were already on a
trajectory for long and thin morphology at
FETAL GROWTH PATTERNS
birth by the second trimester. Previous work
suggests that these observations may reflect
fetal entrainment of maturational rate, as
earlier menarcheal age occurred among adolescent girls who were long and thin at birth
in a population-based study (Adair, 2001).
Moreover, in the present sample high female
third trimester leg growth rates predicted
shorter length and higher ponderal index at
birth. It can by hypothesized that these girls
were comparatively later maturers, by reference to the previous observation identifying
later menarcheal ages among adolescent
girls who were relatively short and heavy at
birth (Adair, 2001).
By contrast, boys with high EFW in the
second trimester were on a trajectory for
higher PI at birth. By the third trimester,
high leg growth rates predicted decreasing
PI. Thus, boys with low PI at birth may
have been poor growers overall by the second
trimester as a result of first trimester factors, a finding in line with previous reports
(Brown et al., 2002), or they may have been
robust third trimester growers. The importance of maternal energy resources for third
trimester leg growth has been previously
reported (Neufeld et al., 1999a). Long and
thin morphology at birth may reflect a
much more demanding energetic stress
in males whose delayed growth trajectory
puts them at greater risk for managing diminishing maternal resources during the third
trimester.
Thus, low PI (or weight) at birth may have
a very different meaning in terms of the
contributory biological patterns for the
sexes, reemphasizing the questionable
meaning of birth size as a predictive variable
(Wilcox, 2001). These data suggest that
mixed sex analyses are likely to err in their
description of fetal growth pattern effects
and trimester-focused analyses of benefits
and insults on birth outcome are not likely
to reveal details of growth chronology.
Mechanisms for sex-specific growth patterns
have been described (Davey et al., 1999). The
present study observations support previous
reports identifying the importance of both
second (Abrams and Selvin, 1995; Hediger
et al., 1989; Li et al., 1998; Metcoff, 1980)
and/or third (Strauss and Dietz, 1999;
Neufeld et al., 1999a,b) trimester maternal
nutrition on birthweight, length, and ponderal index.
One of the questions arising from these
observations is mechanistic. Does the timing
677
relationship found here, in which growth in
fetal weight precedes growth in leg length,
reflect an energetic relationship? This question bears on an ongoing debate regarding
the temporal relationship between growth in
height and weight (Waterlow, 1994) and is a
proposition in line with reports of weight
accrual preceding linear growth during
recovery from malnutrition (Walker and
Golden, 1988). The energy-driven-growth
line of reasoning necessitates careful attention to the meaning of fetal weight. The
common frame of reference for the concept
of weight is as a monitor of changing body
energy stores. The nomenclature belies the
nature of the measurement. Any estimate
of fetal weight presently employed is a composite of body measurements that is only
predictive of true weight. The upper body
measurements used here to predict weight
focus on the head and abdominal circumference. Other studies have documented that
the latter is likely to have been a good marker of adipose tissue accrual and, thus, a
reasonable proxy for fetal weight (Kehl et
al., 1996). But central to concerns surrounding the well being of the fetus, and articulated by all debates in progress concerning
fetal programming, is neonatal body composition as partitioned into lean body mass and
fat reserves.
Longitudinal data documenting developmental timing in fetal fat formation are
rare. Early histological studies identified
the second trimester as a key period of adipogenesis, with no sex differences and a
proximal/distal gradient (Berg, 1911;
Poissonet et al., 1984). The pattern and
pace of increase in fat cell number, by contrast to fat storage within existing cells, is
only beginning to be carefully documented
longitudinally in the normally growing
human fetus (Enzi et al., 1981). From a physiological viewpoint, it is not likely that there
are distinctive long-term, or linear, trimestral-based differences in bone and body
weight growth, as predicted by the timing
hypothesis. It is much more likely that
there is cross-talk between the two processes
during development, as suggested by changing growth rates in the longitudinal data
presented here.
In fact, the often discussed observation
that there appears to be a trade-off between
growth in body length and weight during
early development has recently been given
a scientific foundation and can now be
678
M. LAMPL AND P. JEANTY
framed more precisely: Both bone and fat
derive from the same stem cell (Pittenger et
al., 1999). This deterministic moment in a
stem cell’s life is prompted by signals from
differentiation factors that influence the
alternative genetic programs that contrast
the functional aspects of chondrocytes,
osteoblasts, and fat cells. This is followed by
activation and proliferation signals, which
interface the environment and the developing organism (Ahdjoudj et al., 2001).
In summary, the longitudinal data in this
study documented that fetal growth progresses by a pulsatile pattern of leg and estimated weight acquisition, not a single peak
and decline process, according to a temporal
clock that was neither accurately characterized by the timing hypothesis, nor universally paced across individuals.
The healthy growing fetuses in this sample exhibited greater incremental growth in
EFW during the second trimester, by comparison with leg length, which increased in
the third trimester.
As the fetal weight estimates are based on
head and abdominal measurements, a careful interpretation of these results is that
they redemonstrate the proximal/distal
growth gradient, and girls were accelerated.
The high predictability of leg length for fetal
weight in the second trimester, by contrast
with the reverse, identifies that if legs grew,
it was likely that the upper body had grown;
but upper body growth may not have been
accompanied by lower leg growth. This
developmental pattern is likely to reflect
fetal blood flow characteristics and to
express both developmental timing and
energy shortfall that preferences the upper
body (Lampl et al., 2003). By the third trimester, upper body growth was highly predictive
of leg length in boys, but less so in girls,
whose third trimester leg length was already
predicted by second trimester upper body
growth.
The pulsatile patterns identified in these
data corroborate previous reports of nonlinear and discontinuous fetal growth patterns based on time-intensive longitudinal
data (Bernstein et al., 1996, 1999), clarify
the specifics of individual fetal growth velocity variability (Guihard-Costa, 2000), and
are in line with a saltatory growth process
during infancy (Lampl et al., 1992).
Individual variability in pulse pattern timing
within and between leg growth and estimated fetal weight suggests a functional
relationship in the temporal trajectories
compatible with an underlying nonlinear
dynamic process. This would be a highly
adaptive strategy, one commonly found in
biological systems designed for high flexibility in their function (Pincus, 1995). A dynamical growth process would permit
coordinated development in size and body
proportionality by pathways that translate
available resources into changing growth
rates. These observations suggest that
growth pulse pattern changes are a central
adaptive strategy and underlie sex differences in developmental timing. Differences
in body proportionality at birth may reflect
differences in the developmental timing of
nonlinear growth patterns. The chronology
of growth, and the precise point on the
trajectory between pulses in weight and
length that coincides with an individuals’
birth, may be very important in determining
birth outcome in body proportion. This is a
hypothesis-generating study and these
propositions remain to be tested in future
investigations.
The present data document a pulsatile
fetal growth process that accommodates sex
and individual developmental differences in
growth timing. Further research on fetal
body composition is needed to clarify the
physiology of energy storage and utilization
as it applies to the process of fetal growth.
Sex differences are likely to be found. Recent
scientific evidence suggests that it is improbable that the linear sequence outlined by the
timing hypothesis is physiologically accurate. It is more reasonable to posit that a
synergistic, nonlinear, and dynamic paradigm will be the explanatory framework for
fetal growth and development.
LITERATURE CITED
Abrams B, Selvin S. 1995. Maternal weight gain pattern
and birth weight. Obstet Gynecol 86:163–169.
Adair LS. 2001. Size at birth predicts age at menarche.
Pediatrics 107:E59.
Ahdjoudj S, Lasmoles F, Oyajobi BO, Lomri A, Delannoy P,
Marie PJ. 2000. Reciprocal control of osteoblast/chondroblast and osteoblast/adipocyte differentiation of
multipotential clonal human marrow stromal F/S.
Pediatr Res 47:578–585.
Barker DJP. 1995. Fetal origins of coronary heart disease. Br Med J 311:171–174.
Barker DJP, Osmond C, Golding J, Kuh D, Wadsworth
ME. 1989. Growth in utero, blood pressure in childhood and adult life, and mortality from cardiovascular
disease. Br Med J 298:564–567.
Barker DJ, Osmond C, Simmonds SJ, Wield GA. 1993.
The relation of small head circumference and thinness
FETAL GROWTH PATTERNS
at birth to death from cardiovascular disease in adult
life. Br Med J 306:422–426.
Berg. 1911. Über die Anlage und Entwicklung des
Fettgewebes beim Menschen. Z Morphol Anthropol
13:305–341.
Bernstein IM, Badger GJ. 1999. The pattern of normal
fetal growth. In: Lampl M, editor. Saltation and stasis
in human growth and development. London: SmithGordon. p 27–32.
Bernstein IM, Blake K, Wall B, Badger GH. 1996.
Evidence that normal fetal growth can be noncontinuous. Obstet Gynecol Surv 51:213–214.
Blake KV, Gurrin LC, Beilin LJ, Stanley FJ, Kendall GE,
Landau LI, Newnham JP. 2002. Prenatal ultrasound
biometry related to subsequent blood pressure in childhood. J Epidemiol Community Health 56:713–718.
Brown JE, Murtaugh MA, Jacobs DR Jr, Margellos HC.
2002. Variation in newborn size according to pregnancy weight change by trimester. Am J Clin Nutr
76:205–209.
Cacciari E, Salardi S, David C, Tassinari D, Dalla Casa C,
Pilu GL, Mainetti B, Gualandi S, Bovicelli L. 2000. Is
statural growth predictable in utero? Follow-up from
the second trimester of gestation to the 8th year of life.
J Pediatr Endocrinol Metab 13:381–386.
Crequat J, Duyme M, Brodaty G. 2000. Biometry 2000.
Fetal growth charts by the French College of fetal
ultrasonography and the Inserm U 155. Gynecol
Obstet Fertil 28:435–445.
Davey HW, Wilkins RJ, Waxman DJ. 1999. STAT5 signaling in sexually dimorphic gene expression and
growth patterns. Am J Hum Genet 65:959–965.
DeJong CL, Gardosi J, Baldwin C, Francis A, Dekker
GA, van Geijn HP. 1998. Fetal weight gain in a serially
scanned high-risk population. Ultrasound Obstet
Gynecol 11:39–43.
Enzi G, Zanardo V, Caretta F, Inelmen EM, Rubaltelli F.
1981. Intrauterine growth and adipose tissue development. Am J Clin Nutr 34:1785–1790.
Guihard-Costa AM, Larroche J-C. 1995. Fetal biometry.
Fetal Diagn Ther 10:215–278.
Guihard-Costa AM, Droullé P, Thiebaugeorges O,
Hascoet JM. 2000. A longitudinal study of fetal growth
variability. Biol Neonate 78:8–12.
Hediger ML, Scholl TO, Belsky DH, Ances IG, Salmon
RW. 1989. Patterns of weight gain in adolescent pregnancy: effects on birth weight and preterm delivery.
Obstet Gynecol 74:6–12.
Jeanty P, Dramaix-Wilmet M, van Kerkem J, Petroons P,
Schwers J. 1982. Ultrasonic evaluation of fetal limb
growth. Radiology 143:751–754.
Jeanty P, Cantraine F, Romero R, Cousaert E, Hobbins
JC. 1984a. A longitudinal study of fetal weight growth.
J Ultrasound Med 3:321–328.
Jeanty P, Cousaert E, Cantraine F. 1984b. Normal
growth of the abdominal perimeter. Am J Perinatol
1:129–135.
Jeanty P, Cousaert E, Hobbins JC, Tack B, Bracken M,
Cantraine F. 1984c. A longitudinal study of fetal head
biometry. Am J Perinatol 1:118–128.
Kehl RJ, Krew MA, Thomas A, Catalano PM. 1996. Fetal
growth and body composition in infants of women
with diabetes mellitus during pregnancy. J Matern
Fetal Med 5;273–280.
Kramer MS, McLean FH, Olivier M, Willis DM, Usher
RH. 1989. Body proportionality and head and length
‘sparing’ in growth-retarded neonates: a critical reappraisal. Pediatrics 84:717–723.
Kuzawa CW. 2001. Maternal nutrition, fetal growth, and
cardiovascular risk in Filipino adolescents. Ph.D. dissertation. Ann Arbor, MI: University Microfilms.
679
Lampl M, Veldhuis JD, Johnson ML. 1992. Saltation and
stasis: a model of human growth. Science 258:801–803.
Lampl M, Kuzawa CW, Jeanty P. 2003. Prenatal smoke
exposure alters growth in limb proportions and head
shape in the midgestation human fetus. Am J Human
Biol 15:533–546.
Law CM, Barker DJ, Osmond C, Fall CH, Simmonds SJ.
1992. Early growth and abdominal fatness in adult
life. J Epidemiol Community Health 46:184–186.
Li R, Haas JD, Habicht J-P. 1998. Timing of the influence of maternal nutritional status during pregnancy
on fetal growth. Am J Hum Biol 10:529–539.
Martinez-Morales S, Bonillo-Perales A, Munoz-Hoyos A,
Puertas-Prieto A, Uberos-Fernandez J, MolinaCarballo A, Bonillo-Perales JC, Sabatel-Lopez R.
1999. The influence of maternal erythrocyte deformability on fetal growth, gestational age and birthweight. J Perinat Med 27:166–172.
Metcoff J. 1980. Maternal nutrition and fetal development. Early Hum Dev 4:99–120.
Neufeld L, Pelletier DL, Haas JD. 1999a. The timing of
maternal weight gain during pregnancy and fetal
growth. Am J Hum Biol 11:627–637.
Neufeld L, Pelletier DL, Haas JD. 1999b. The timing
hypothesis and body proportionality of the intrauterine growth retarded infant. Am J Hum Biol
11:638–646.
Okazaki R, Inoue D, Shibata M, Saida M, Kido S, Ooka H,
Tomiyama H, Sakamoto Y, Matsumoto T. 2002.
Estrogen promotes early osteoblast differentiation
and inhibits adipocyte differentiation in mouse
bone marrow stromal cells lines that express estrogen
receptor (ER) alpha or beta. Endocrinology 143:
2349–2356.
Petersen S, Larsen T, Greisen G. 1992. Judging fetal
growth from body proportions at birth. Early Hum
Dev 30:139–146.
Pincus SM. 1995. Quantifying complexity and regularity
of neurobiological systems. Methods Neurosci 28:
336–363.
Pittenger MF, Mackay AM, Beck SC, Jaiswal RK,
Douglas R, Mosca JD, Moorman MA, Simonetti DW,
Craig S, Marshak DR. 1999. Multilineage potential of
adult human mesenchymal stem cells. Science
284:143–147.
Poissonnet CM, Burdi AR, Garn SM. 1984. The chronology of adipose tissue appearance and distribution in
the human fetus. Early Hum Dev 10:1–11.
Smith GD, Greenwood R, Gunnell D, Sweetnam P,
Yarnell J, Elwood P. 2001. Leg length, insulin resistance, and coronary heart disease risk: the Caerphilly
Study. J Epidemiol Community Health 55:867–872.
Sorensen HT, Sabroe S, Rothman KJ, Gillman M,
Steffensen FH, Fischer P, Sorensen TI. 1999. Birth
weight and length as predictors for adult height. Am
J Epidemiol 149:726–729.
Stein AD, Ravelli AC, Lumey LH. 1995. Famine, thirdtrimester pregnancy weight gain, and intrauterine
growth: the Dutch Famine Birth Cohort Study. Hum
Biol 67:135–150.
Strauss RS, Dietz WH. 1999. Low maternal weight gain
in the second or third trimester increases the risk for
intrauterine growth retardation. J Nutr 5:988–993.
Suzuki T, Minami J, Ohrui M, Ishimitsu T, Matsuoka H.
2000. Relationship between birth weight and cardiovascular risk factors in Japanese young adults. Am J
Hyper 13:907–913.
Tanner JM. 1978. Fetus into man, 1st ed. Cambridge,
MA: Harvard University Press.
Tanner JM. 1990. Fetus into man, 2nd ed. Cambridge,
MA: Harvard University Press. p 41.
680
M. LAMPL AND P. JEANTY
Valdez R, Athens MA, Thompson GH, Bradshaw BS,
Stern MP. 1994. Birthweight and adult health outcomes
in a biethnic population in the USA. Diabetologia
37:624–631.
Vik T, Vatten L, Jacobsen G, Bakketeig LS. 1997. Prenatal
growth in symmetric and asymmetric small-for-gestational-age infants. Early Hum Dev 25:167–176.
Villar J, Belizan JM. 1982. The timing factor in the
pathophysiology of the intrauterine growth retardation syndrome. Obstet Gynecol Surv 37:499–506.
Walker SP, Golden MH. 1988. Growth in length of children recovering from severe malnutrition. Eur J Clin
Nutr 42:395–404.
Waterlow JC. 1994. Relationship of gain in height
to gain in weight. Eur J Clin Nutr 48(Suppl 1):
S72–S74.
Wilcox AJ. 2001. On the importance—and the unimportance—of birthweight. Int J Epidemiol 30:1233–1241.
Zaren B, Lindmark G, Bakketeig L. 2000. Maternal
smoking affects fetal growth more in the male fetus.
Paediatr Perinat Epidemiol 14:118–126.
Ziegler B, Johnsen SP, Thulstrup AM, Engberg M,
Lauritzen T, Sorensen HT. 2000. Inverse association
between birth weight, birth length and serum total
cholesterol in adulthood. Scand Cardiovasc J
34:584–588.