Reliable antenatal identification of growth-restricted infants at risk of adverse outcomes might be expected to improve allocation of monitoring resources, with the possibility of improving perinatal outcomes. Growth velocity standards quantify fetal growth from two ultrasound measurements1 provided the interval between measurements and gestational age at second measurement are known. Fetal growth velocity has been described as potentially valuable for antenatal prediction of growth-restricted infants and intrapartum heart rate abnormalities.2,3
The distinction between growth-restricted and constitutionally small infants is well recognized, as is the limited importance of birth weight as an indicator of fetal growth achievement and perinatal outcome.4 Abnormalities of neonatal body constitution appear to be more useful indicators of adverse short- and long-term outcomes than birth weight alone.5–7 Yet, only a few studies have used neonatal anthropometric criteria to diagnose fetal growth restriction (FGR).2,8
Using absence of an increment in fetal abdominal circumference measurement as their definition of FGR, Mongelli et al9 found that shortening of intermeasurement interval resulted in increased false-positive diagnosis rates for FGR. However, that analysis was limited because of the lack of an appropriate standard for the confirmation of FGR. Against that background we decided to investigate the influence of between-measurement interval on diagnostic performance of fetal growth velocity for predicting three different neonatal anthropometric criteria of FGR.
Materials and Methods
Three hundred thirteen women who attended the antenatal clinic at Ninewells Hospital (Dundee, Scotland) were enrolled, the details of which were presented in detail elsewhere.1 Entry criteria were singleton pregnancy, gestational age less than 85 days confirmed by crown-rump length measurement, and absence of recognized risk factors of accelerated or restricted fetal growth, including history of small for gestational age (SGA) infants, existing medical disorders, or heavy smoking (more than 20 cigarettes per day). All subjects were sequentially entered into one of the four scheduled scanning schedules:
- 22, 26, 30, 32, 34, 36, 38, 40 weeks (n = 72)
- 23, 27, 31, 33, 35, 37, 39, 41 weeks (n = 72)
- 24, 28, 32, 34, 36, 38, 40 weeks (n = 63)
- 25, 29, 33, 35, 37, 39, 41 weeks (n = 67)
- (n = number continuing in the study).
Ultrasound measurements were made using an Aloka SSD-650 (Aloka Co. Ltd., Mitakashi, Tokyo, Japan) real-time ultrasound scanner with a 3.5-MHz probe, by the same observer (PO). Crown-rump length was measured in a standard manner10 and gestational age calculated with reference to that measurement.11 The fetal abdominal area was measured at the level of the umbilical vein by tracing the outline of the trunk on-screen.12 Three measurements were made and the mean recorded. Intraobserver reproducibility was assessed by measuring ten volunteers outside the study in the third trimester. The coefficient of variation was 1.45%.
Birth weight was adjusted to account for mothers' height and midpregnancy weight, and accorded a centile position according to gestational age, sex, and birth order.13 Skinfold thickness was measured on the second or third day of life using Holtain calipers (CMS Weighing Equipment, London, England). Three measurements were made at the infant's subscapular and triceps areas, the mean measurement recorded, and a centile position measured after adjustment for gestational age and sex.14 The occipitofrontal circumference was measured with a tape measure and the mean of three measurements recorded. Midarm circumference was measured at the point halfway between acromion and olecranon process of the ulna on the right arm, flexed at 90°. The mean of three measurements was recorded, the midarm circumference–to–occipitofrontal circumference ratio calculated, and ratios compared with gestational age–adjusted reference data.15 Neonatal length was measured on a standard neonatal anthropometer on the third day of life. The mean of three measurements was recorded, the ponderal index calculated, and centile position recorded.16 Neonatal measurements were made by one investigator (PO) without knowledge of fetal growth velocity calculations. Ethical approval for the study was obtained from the local Research Ethics Committee.
Fetal growth velocity was determined for four intervals and gestational ages: at 2-week intervals using the last measurement before delivery, at 4-week intervals using the last measurement before delivery, at 6-week intervals using the last measurement before delivery, and at 4-week intervals in the early third trimester (included to examine the influence of proximity to delivery time on test performance). The velocity standard deviation score represents the gestational age–adjusted mean daily increment between the two measurements and was calculated from the following formula:
The reference mean increment and standard deviation refer to the gestational age-specific values determined from published reference ranges for ultrasound growth velocity established from the same population.1 The gestational ages of the reference values were the second fetal measurements used in the calculations of daily increments.
We analyzed the data using receiver operating characteristic (ROC) curves in the first instance because when there are many tests and outcomes, the area under the ROC curve is considered the best discriminator of diagnostic performance. In ROC analysis, the sensitivity is plotted against 1–specificity, and this plot provides an opportunity to define the cutoff points for classifying positive and negative cases for test results on a continuous scale. We used an iterative process to determine a cutoff point that maximized specificity of the various growth velocity measurements because in conditions of low prevalence such as FGR, a diagnostic test would be more useful if a positive result ruled in disease (ie, a test with high specificity). For each cutoff point we calculated the likelihood ratio, defined as sensitivity/(1–specificity). That calculation is a clinically useful measure of test accuracy that enables one to quantify the effect a particular test result has on the probability of a certain outcome.
Using a simplified form of Bayes' theorem:
For a positive test result, likelihood ratios exceeding 10 generate significant changes in the pretest probability of growth restriction, whereas likelihood ratios of 5–10 generate only moderate changes. For a negative result, likelihood ratios less than 0.1 generate statistically significant changes, whereas likelihood ratios of 0.1–0.2 generate only moderate changes in the pretest probability.17
The power of our sample was explored according to the method proposed by Simel et al.18 We were interested in the impact of the test result on the likelihood of disease, particularly that of a positive test result in accurately predicting FGR. That emphasis meant that we wanted a high value of likelihood ratio for a positive test result with a minimum clinically important likelihood ratio threshold of 10.17 Based on a previous study2 that involved the same population, we assumed a disease prevalence of 10%, a sensitivity of 55%, and a specificity of 90%, which allowed us to estimate that approximately 203 cases (including 18 with FGR) were required for an appropriately narrow confidence interval (CI) around a clinically meaningful likelihood ratio value. The total number of women who continued in the study was 274, but the number available for analysis varied according to 12 combinations of measurement interval and criterion for diagnosis of FGR.
Among the 274 women who continued in the study, mean maternal age was 26 years, with 148 (54%) in their first pregnancies. Two hundred sixty infants (95%) were delivered at 37 weeks' gestation or later. Twenty-two (8%) had adjusted birth weights below the tenth percentile, among whom 11 (4%) also were below the third percentile. Skinfold thickness, ponderal index, and midarm circumference–to–occipitofrontal circumference ratios were available in 238, 257, and 237 cases, respectively. Some cases were missed because of early discharge, or could not be categorized because the reference data for neonatal anthropometry used did not extend to preterm births. Twenty-six infants (10.9%) had one or both skinfold thicknesses under the tenth centile, 40 (15.6%) had a ponderal index under 25th centile, and 17 (7%) cases had midarm circumference–to–occipitofrontal circumference ratios below 21 standard deviation.
The median interval and range in days for 2-week, 4-week, 6-week, and early third trimester groups were 14 (11–21), 28 (22–30), 42 (31–57), and 28 (21–37), respectively. For the early third trimester 4-week interval, the median and range of gestational ages for the first and second measurements used to calculate velocity were 32 weeks (range 27–33) and 36 weeks (32–37), respectively.
The areas under the ROC curves, together with sensitivity and specificity for the different velocity calculations are presented in Table 1. Velocity intervals have some discriminatory capacity for the three criteria of FGR, but that is highest for the 4- and 6-week intervals. The test performances are further described by the likelihood ratios presented in Table 2. As anticipated from the analysis of the ROC curve areas, the 4-and 6-week intervals (both using the last measurement before delivery) had the highest likelihood ratios for a positive test. With the exception of predicting infants with a midarm circumference–to–occipitofrontal circumference ratio of under 21 SD, the 4-week interval had higher likelihood ratios than the 6-week velocity interval, which suggests that a 4-week between-measurement interval will optimize performance of fetal growth velocity for predicting FGR. The likelihood ratios for the 2- and 4-week interval in the early third trimester are low for all three criteria of FGR, suggesting that those intervals and timings of measurements are not useful for predicting FGR.
Single estimates of fetal size and measurements of fetal body proportionality do not accurately predict infants with anthropometric features of intrauterine malnour-ishment.19,20 Serial fetal measurements, however, may show the dynamic processes of normal and abnormal fetal growth, but quantification and interpretation of serial fetal biometry is potentially fraught with difficul-ties.21 One approach to quantifying serial fetal measurements is the calculation of a growth velocity standard deviation score using values for gestational age-specific daily growth increment means and standard deviations.1 Calculating fetal growth velocity that way was described in the prediction of infants with FGR and pregnancies that required intrapartum cesarean delivery for fetal heart rate abnormality.2,3 In our department, fetal abdominal area measurement is preferred to abdominal circumference because circumference measurements are appropriate when the outline is circular, but only the area is truly representative of a cross-sectional fetal profile if the outline is elliptical.22
Several observational studies support measurements of neonatal anthropometry or ratios of actual to expected birth weight in identifying infants who had intrauterine malnourishment and adverse consequences.5–7 Describing fetal growth achievement in terms of a ratio of actual birth weight to an expected optimal birth weight more usefully identifies infants with low skin-fold thicknesses and other features of FGR than birth weight alone.23 For those reasons, we have chosen to classify the infants in this study as growth-restricted or not on the basis of three anthropometric measures and not on birth weight. No data are available to instruct us about the relative importance of the three described anthropometric measures in terms of perinatal and long-term performance so we included results of all three.
Standard deviation scores are increasingly used in studies of prenatal ultrasound to describe fetal size and growth2,24 because they provide more precise estimates of fetal size and growth than a description of above or below a particular centile, which might under- or overestimate any growth delay. Standard deviation scores also allow us to describe fetal biometry independent of gestational age, whereas traditional centile charts do not permit comparison of different fetuses at different gestational ages. A standard deviation score of zero is the 50 th centile and scores of 1.25 and −1.25 approximate to the 90th and 10th centiles, respectively.
We used likelihood ratios to evaluate growth velocity because expressing performance of a test in those terms enables us to assess how useful the test might be in clinical practice, which depends on change in pretest probability from the test result. We believe that is the best method of evaluating diagnostic tests. Traditionally, concepts of sensitivity and specificity are used to assess diagnostic tests but these values are less useful. Evidence of usefulness of a test is considered very strong when the likelihood ratio exceeds 10.17
Among a population of SGA fetuses, Chang et al8 found that change in abdominal circumference or estimated fetal weight was useful for identifying those with anthropometric features of FGR, but they did not address influence of between-measurement interval or proximity of last measurement to delivery. We found that calculating fetal growth velocity with standards in the current study were useful in identifying growth-restricted infants when a 4-week measurement interval is used.2 The present study is an extension of our earlier work examining influence of between-measurement interval on fetal growth velocity. The results of this study are in broad agreement with the simulation model of Mongelli et al,9 who concluded that an interval of at least 3 weeks was necessary to minimize the false-positive rate of diagnosis of FGR; our study had the advantage of using actual cases with appropriate standards for quantifying growth and appropriate anthropometric categorization of growth restriction.
There are many possible explanations for our observations. The 2-week interval probably works poorly because measurement variation will have a greater influence on velocity calculations compared with 4- and 6-week intervals. Reducing the coefficient of variation of the ultrasound measurements reduces the rate of false-positive diagnoses.9 There is only a small difference in likelihood ratios between 4- and 6-week measurement intervals, with 4-week results slightly better. That finding is probably because growth restriction resulting in anthropometric features of malnourishment in neonates occurs late in pregnancy, and growth failure is likely to be diluted by more normal growth in the preceding 1–3 weeks when a 6-week interval is used. That assumption could be explored further by analyzing growth velocity calculated with varying between-measurement intervals at specific gestational ages.
In this study, a 4-week interval earlier in the third trimester did not usefully identify growth-restricted fetuses, presumably because (in a low-risk population at least) growth failure is not manifest at that point, which raises important issues regarding applicability of growth velocity calculations when screening for FGR. Test performance over a 4-week interval was good when the last measurement before delivery was used, but establishing which is the last measurement before delivery can be made only retrospectively. Test performance appears to be poor at earlier gestational ages, thus suggesting that calculating growth velocity is likely to have only limited clinical application when screening for FGR in low-risk populations. Further work is necessary to find whether a 4-week measurement interval in the early third trimester is useful for identifying growth abnormalities in high-risk populations, and if so whether that information can be translated into improved obstetric management.
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© 2001 The American College of Obstetricians and Gynecologists
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