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DOI: 10.1055/s-0044-1788810
Normative Data of Ulnar Length in Pediatric Indian Population
Abstract
Objective The aim of this study is to create clinical normative data for ulnar length in the pediatric population and to demonstrate the usefulness of such data.
Materials and Methods A nationally representative sample of healthy children aged 1 day to 18 years from five centers across India was collected. The percutaneous length of the ulna was measured by using a certified calibrated measuring tape across all centers. Other variables such as geographical domicile, dominance of the hand, age, body mass index (BMI), and sex of the child were also recorded.
Results In total, 1,300 children (883 males and 417 females) with age ranging from 1 day to 18 years were included in the study. Gradual lengthening of the ulna was seen in both male and female children with increasing age without a significant difference; however, at 8, 9, and 14 years, there was significant lengthening of the ulna in males compared with females although the difference was statistically insignificant at 17 years. Apropos BMI at 16 years of age, a longer ulna was observed in obese children. Later on, at 18 years, the difference in ulnar length was insignificant. South Indian children had a significantly longer ulna up to the age of 11 years, but after the age of 11 years there was no difference in ulnar length in all zones. The length of the ulna was not affected by hand dominance. There was good inter-observer agreement and reliability between different centres. Age, zone, and gender, had statistically significant effect on the length of ulna but BMI and hand dominance was not significant.
Conclusion This multicentric study provides normative data on the percutaneous length of the ulna in the Indian pediatric population. Gradual lengthening of the ulna was seen in all children with increasing age. The length of the ulna was significantly more in male, obese, and in South Indian children. However, except for age, other factors become insignificant at maturity.
#
Introduction
The length of the ulna has been commonly used for measurement of the growth of the forearm.[1] [2] Normative data on ulnar length allow an estimation of the effect of congenital, traumatic, neoplastic, or metabolic abnormalities on the forearm growth and function.[3] The measurements would also help in developing age- and population-specific orthopaedic implants, intraoperative decision-making, and studying and validating the functional outcomes of the forearm bones both before and after surgical reconstruction. The length of the ulna can also be used as a surrogate marker to calculate the height and predict pulmonary function in children.[4] [5] Therefore, knowledge of the normal dimensions of the ulna is vital for anatomists, hand surgeons, forensic scientists, and anthropological archeologists. There are multiple studies analyzing the ulnar length; however, almost all of them have been done in adults, dry bone, or in cadavers and/or have been done in the western population.[6] [7] There are no Indian normative data of ulnar length measurement in the pediatric age groups; therefore, the aim of this study is to establish a normal database of the length of the ulna in different age groups and gender belonging to a sample of the pediatric population in India.
#
Materials and Methods
This is an observational, prospective, multicentric study conducted over a period of 10 months from January to October 2022 in the Department of Plastic, Hand and Reconstructive Surgery at five centers (Mumbai, Chennai, Manipal, Jabalpur, and Srinagar) across India. A total of 1,300 normal children and 2,600 ulnae were sampled for this study. All departments involved took ethical committee permissions from their respective hospitals. Informed consent from parents/legal guardians and children's assent where appropriate was taken for measurement.
All children, aged 1 day to 18 years, attending the hand surgery, plastic surgery, and pediatric medicine outpatient department were sampled. The children were apparently healthy and without physical deformity. Siblings coming along with a patient were also recruited after adequate consent of the parents/assent of the child. Equal representation of the sexes was attempted across all age groups. Children with developmental disorders affecting the musculoskeletal development, systemic malignancies, past history of bony injuries, arthritic changes of any etiology, infection, or bone or soft-tissue disease were excluded.
The sample size was calculated using the level of precision (sampling error-d) to be 5% (0.05) with a 95% confidence level, and the Z score (at 5%) was 1.96. The degree of variability (P) was taken as 0.5 considering the Indian populations to be highly heterogeneous and diverse. According to the formula, the sample size was 384 ulnae per center. The proposed sample size was taken as 400 ulnae in 200 participants per center.
Percutaneous length of the ulna was measured using a certified calibrated measuring tape (Cescorf anthropometric tape manufactured by NutriActiva, LLC, Bloomington, MN, United States), which was supplied to all units, and all the principal investigators and co-investigators of the partner center were trained on the methodology through online meetings. The percutaneous length of the ulna was measured with the elbow flexed and palm placed over the opposite shoulder and marking the tips of the olecranon and styloid processes of the ulna. The distance between the proximal and distal landmarks was measured using a measuring tape. Length was measured independently on both the right and left sides ([Figs. 1] and [2]). All measurements were taken between 11 a.m. and 3 p.m. to eliminate diurnal variations. Each measurement was taken by two observers separately in centimeters and an average of two readings was taken to avoid any errors in measurement. An officially certified and calibrated measuring tape was used by all associated centers. Apart from the percutaneous length of the ulna, geographical domicile, vis-à-vis, part of India (north, central, west, and south zones), dominance of the hand with the age and sex of the child, height, and weight were also recorded. The body mass index (BMI) was calculated and the child was categorized as normal (BMI of 18.5–24.9), overweight (BMI of 25–29.9), or obese (BMI ≥30). In addition, the mother tongue was noted from a population diversity point of view in the Indian context.
The data were analyzed using IBM-SPSS version 23.0 and expressed in sample mean and standard deviation. A p-value less than 0.05 was considered statistically significant. The statistical methods used were nonparametric tests Mann–Whitney U test and Kruskal–Wallis one way analysis of variance for more than two variables. Intra- and interobserver comparisons were done using intraclass correlation coefficient (ICC) test. An ICC value between 0.75 and 0.90 was considered as good intraclass reliability. Any bias was eliminated by using two independent measurements by different examiners and multiple regression analysis with a variance inflation factor (VIF).
#
Results
A total of 1,300 children (2,600 ulnae) were included in the study. The demographic data, such as gender, age, BMI, hand dominance, and geographical domicile, are shown in [Table 1] ([Fig. 3]).
Gradual lengthening of the ulna was seen in all children with increasing age with a significant difference; till 7, 10 and between 13–14 years. After 14 years though the ulna length continues to grow but did not achieve statistical significance. (p = 0.816 and 0.956; [Table 2] and [Fig. 4]).
|
Age (y) |
Mean right ulnar length (cm) |
Mean left ulnar length (cm) |
Right p-Value[a] |
Left p-Value[a] |
|---|---|---|---|---|
|
Mean ± SD |
Mean ± SD |
|||
|
1 |
9.69 ± 2.68 |
9.56 ± 1.94 |
0.000 |
0.000 |
|
2 |
12.13 ± 2.84 |
12.15 ± 3.23 |
0.002 |
0.005 |
|
3 |
12.91 ± 1.76 |
12.90 ± 1.68 |
0.000 |
0.000 |
|
4 |
14.56 ± 2.27 |
14.35 ± 1.86 |
0.021 |
0.152 |
|
5 |
15.06 ± 2.10 |
15.04 ± 2.11 |
0.000 |
0.000 |
|
6 |
16.88 ± 4.10 |
16.49 ± 1.40 |
0.025 |
0.381 |
|
7 |
17.26 ± 1.56 |
17.35 ± 1.56 |
0.001 |
0.003 |
|
8 |
18.89 ± 2.42 |
18.95 ± 2.46 |
0.442 |
0.572 |
|
9 |
19.19 ± 2.24 |
19.31 ± 2.27 |
0.054 |
0.113 |
|
10 |
19.97 ± 2.48 |
20.13 ± 2.55 |
0.000 |
0.001 |
|
11 |
21.94 ± 1.73 |
22.04 ± 1.74 |
0.115 |
0.345 |
|
12 |
22.52 ± 2.33 |
22.87 ± 1.71 |
0.763 |
0.475 |
|
13 |
22.92 ± 2.34 |
23.02 ± 2.37 |
0.007 |
0.030 |
|
14 |
24.20 ± 1.92 |
24.42 ± 1.91 |
0.029 |
0.031 |
|
15 |
25.74 ± 2.04 |
25.78 ± 2.06 |
0.716 |
0.986 |
|
16 |
25.76 ± 1.90 |
22.54 ± 2.73 |
0.861 |
0.690 |
|
17 |
25.39 ± 2.00 |
25.69 ± 2.23 |
0.151 |
0.211 |
|
18 |
26.91 ± 1.41 |
27.21 ± 1.38 |
0.816 |
0.956 |
a By Mann–Whitney U test.
The gradual lengthening of the ulna was seen in both male and female children with increasing age without significant difference; however, at the age of 8, 9, and 14 years, there was significant lengthening of the ulna in males compared with females although the difference was statistically insignificant at 17 years (p = 0.218; [Table 3]; [Fig. 4]).
|
Age (y) |
Mean left ulnar length (cm) |
p-Value |
Mean right ulnar length (cm) |
p-Value[a] |
||
|---|---|---|---|---|---|---|
|
Male |
Female |
Male |
Female |
|||
|
Mean ± SD |
Mean ± SD |
Mean ± SD |
Mean ± SD |
|||
|
1 |
9.75 ± 2.21 |
9.58 ± 3.51 |
0.117 |
9.7 ± 2.04 |
9.26 ± 1.66 |
0.132 |
|
2 |
12.3 ± 3.21 |
11.72 ± 1.51 |
0.111 |
12.32 ± 3.69 |
11.75 ± 1.55 |
0.145 |
|
3 |
13.01 ± 1.77 |
12.69 ± 1.71 |
0.620 |
12.97 ± 1.62 |
12.75 ± 1.8 |
0.857 |
|
4 |
14.46 ± 1.99 |
14.77 ± 2.77 |
0.765 |
14.39 ± 2.05 |
14.27 ± 1.42 |
0.746 |
|
5 |
15 ± 2.38 |
15.21 ± 1.2 |
0.693 |
14.95 ± 2.38 |
15.27 ± 1.22 |
0.972 |
|
6 |
16.97 ± 4.74 |
16.61 ± 1.38 |
0.630 |
16.41 ± 1.44 |
16.71 ± 1.29 |
0.550 |
|
7 |
17.47 ± 1.52 |
16.92 ± 1.61 |
0.253 |
17.55 ± 1.45 |
17.02 ± 1.7 |
0.267 |
|
8 |
19.4 ± 1.69 |
17.46 ± 3.54 |
0.049 |
19.51 ± 1.74 |
17.38 ± 3.47 |
0.033 |
|
9 |
19.79 ± 1.95 |
18.33 ± 2.39 |
0.005 |
19.9 ± 1.96 |
18.45 ± 2.46 |
0.012 |
|
10 |
20.18 ± 2.48 |
19.72 ± 2.52 |
0.828 |
20.1 ± 3.04 |
20.16 ± 1.89 |
0.548 |
|
11 |
21.76 ± 1.64 |
22.16 ± 1.86 |
0.363 |
21.86 ± 1.77 |
22.25 ± 1.76 |
0.525 |
|
12 |
22.8 ± 1.9 |
21.89 ± 3.08 |
0.536 |
22.91 ± 1.87 |
22.8 ± 1.33 |
0.727 |
|
13 |
23.19 ± 2.25 |
22.51 ± 2.48 |
0.511 |
23.28 ± 2.23 |
22.63 ± 2.59 |
0.636 |
|
14 |
24.8 ± 1.75 |
22.83 ± 1.62 |
0.014 |
24.99 ± 1.82 |
23.12 ± 1.45 |
0.004 |
|
15 |
26.01 ± 2.2 |
25.00 ± 1.45 |
0.343 |
26.04 ± 2.23 |
25.06 ± 1.44 |
0.391 |
|
16 |
26.18 ± 1.78 |
24.48 ± 1.77 |
0. |
25.87 ± 2.95 |
24.55 ± 1.82 |
0.476 |
|
17 |
25.78 ± 2.59 |
24.8 ± 0.29 |
0.218 |
26.06 ± 2.91 |
25.13 ± 0.25 |
0.218 |
|
18 |
26.91 ± 1.41 |
NA |
NA |
27.21 ± 1.38 |
NA |
NA |
Abbreviations: NA, data not available; SD, standard deviation.
a Mann–Whitney U test.
The mean length of the ulna in different age groups according to the geographical zone is shown in [Table 4]. South Indian children had a statistically significantly larger length of the ulna up to 11 years of age; however, such difference was not seen after 11 years of age (p = 1.00 and 0.317; [Table 4]; [Fig. 4]).
|
Age (y) |
Mean left ulnar length (cm) |
p-Value[a] |
Mean right ulnar length (cm) |
p-Value[a] |
||||||
|---|---|---|---|---|---|---|---|---|---|---|
|
Zone |
Zone |
|||||||||
|
Central |
North |
West |
South |
Central |
North |
West |
South |
|||
|
Mean ± SD |
Mean ± SD |
Mean ± SD |
Mean ± SD |
Mean ± SD |
Mean ± SD |
Mean ± SD |
Mean ± SD |
|||
|
1 |
10.29 ± 3.92 |
9.79 ± 1.62 |
9.13 ± 1.55 |
10.04 ± 1.6 |
0.006 |
9.9 ± 2.42 |
9.86 ± 1.61 |
9.14 ± 1.57 |
10.01 ± 1.54 |
0.005 |
|
2 |
12.3 ± 3.73 |
11.9 ± 1.76 |
11.9 ± 1.78 |
12.23 ± 1.27 |
0.971 |
12.31 ± 4.34 |
12.01 ± 1.83 |
11.89 ± 1.76 |
12.3 ± 1.3 |
0.820 |
|
3 |
12.45 ± 1.78 |
13.22 ± 1.12 |
13.21 ± 2.02 |
13.85 ± 0.84 |
0.002 |
12.32 ± 1.7 |
13.37 ± 1.19 |
13.36 ± 1.79 |
13.82 ± 0.71 |
0.001 |
|
4 |
14.55 ± 3.02 |
13.75 ± 0.76 |
14.6 ± 1.38 |
15.25 ± 3.02 |
0.083 |
13.78 ± 1.79 |
13.92 ± 0.82 |
14.61 ± 1.43 |
15.32 ± 3 |
0.076 |
|
5 |
14.8 ± 2.42 |
15.39 ± 1.08 |
14.98 ± 1.38 |
15.9 ± 2.58 |
0.106 |
14.67 ± 2.42 |
15.68 ± 0.98 |
15.01 ± 1.31 |
15.93 ± 2.63 |
0.084 |
|
6 |
16 ± 1.2 |
16.27 ± 1.5 |
18.43 ± 8.18 |
17.25 ± 1.05 |
0.065 |
15.97 ± 1.2 |
16.41 ± 1.55 |
16.53 ± 1.5 |
17.36 ± 0.93 |
0.036 |
|
7 |
16.97 ± 0.93 |
17.18 ± 1.32 |
17.09 ± 2.04 |
18.06 ± 1.18 |
0.282 |
16.9 ± 1 |
17.33 ± 1.41 |
17.21 ± 1.93 |
18.11 ± 1.27 |
0.259 |
|
8 |
18.22 ± 0.77 |
18.69 ± 2.08 |
18.13 ± 3.39 |
20.09 ± 0.58 |
0.152 |
18.22 ± 0.78 |
18.99 ± 2.23 |
18.2 ± 3.4 |
20 ± 0.89 |
0.268 |
|
9 |
16.99 ± 2.43 |
19.52 ± 1.25 |
19.16 ± 2.63 |
20.06 ± 1.32 |
0.063 |
17.11 ± 2.46 |
19.83 ± 1.28 |
19.17 ± 2.66 |
20.19 ± 1.25 |
0.060 |
|
10 |
18.87 ± 2.01 |
20.19 ± 3.41 |
20.47 ± 1.69 |
20.17 ± 2.32 |
0.596 |
18.39 ± 2.64 |
21.08 ± 2.8 |
20.48 ± 1.72 |
20.22 ± 2.44 |
0.229 |
|
11 |
NA |
22.57 ± 1.36 |
20.64 ± 1.35 |
22.33 ± 1.94 |
0.034 |
NA |
22.94 ± 1.43 |
20.55 ± 1.31 |
22.28 ± 1.68 |
0.019 |
|
12 |
NA |
22.65 ± 1.97 |
21.5 ± 3.5 |
23.07 ± 1.53 |
0.570 |
NA |
22.88 ± 1.96 |
22.69 ± 1.75 |
23 ± 1.41 |
0.994 |
|
13 |
22.12 ± 0.9 |
22.62 ± 3.46 |
22.75 ± 1.83 |
24.6 ± 1.52 |
0.130 |
22.07 ± 0.95 |
22.91 ± 3.56 |
22.84 ± 1.9 |
24.5 ± 1.32 |
0.179 |
|
14 |
21.28 ± 0.16 |
24.37 ± 2.03 |
24.37 ± 1.57 |
24.5 ± 1.87 |
0.213 |
21.42 ± 0.45 |
24.78 ± 2.06 |
24.2 ± 1.5 |
24.8 ± 1.48 |
0.165 |
|
15 |
NA |
25.99 ± 2.57 |
25.37 ± 1.19 |
25.5 ± 0.71 |
0.818 |
NA |
26.17 ± 2.57 |
25.33 ± 1.13 |
25 ± 0 |
0.672 |
|
16 |
NA |
26.53 ± 1.84 |
24.98 ± 1.65 |
25.38 ± 2 |
0.324 |
NA |
25.97 ± 3.74 |
25.06 ± 1.7 |
25.38 ± 2 |
0.364 |
|
17 |
NA |
26.16 ± 2 |
25.02 ± 2.34 |
24 ± 1.41 |
0.516 |
NA |
26.7 ± 2.22 |
25.12 ± 2.35 |
24 ± 1.41 |
0.353 |
|
18 |
NA |
26.72 ± 1.44 |
28.1 ± 0.0 |
NA |
1.00 |
NA |
27.1 ± 1.48 |
27.9 ± 0.0 |
NA |
0.317 |
Abbreviations: BMI, body mass index; NA, data not available; SD, standard deviations.
a Kruskal–Wallis test.
The mean length of the ulna, vis-à-vis, BMI in different age groups is shown in [Table 5]. The mean length of the ulna increases in normal, overweight, or obese children similarly up to 15 years of age; however, a significantly longer ulna was seen in obese children at the age of 16 years (p = 0.029; [Table 5]; [Fig. 4]). Nevertheless, the proportion of obese children was only 5%. Later on, at the age of 18 years, the difference in ulnar length was insignificant (p = 0.48).
|
Age (y) |
Mean left ulnar length (cm) |
p-Value[a] |
Mean right ulnar length (cm) |
p-Value[a] |
||||
|---|---|---|---|---|---|---|---|---|
|
BMI |
BMI |
|||||||
|
Normal |
Overweight |
Obese |
Normal |
Overweight |
Obese |
|||
|
Mean ± SD |
Mean ± SD |
Mean ± SD |
Mean ± SD |
Mean ± SD |
Mean ± SD |
|||
|
1 |
9.7 ± 2.77 |
9.5 ± 0.71 |
9.49 ± 2.8 |
0.994 |
9.54 ± 1.97 |
9.5 ± 0.71 |
9.5 ± 2.78 |
0.985 |
|
2 |
12.17 ± 2.96 |
11 ± 0.0 |
NA |
0.304 |
12.18 ± 3.37 |
11 ± 0.0 |
NA |
0.333 |
|
3 |
12.86 ± 1.84 |
NA |
NA |
NA |
12.83 ± 1.74 |
NA |
NA |
NA |
|
4 |
14.71 ± 2.43 |
NA |
14 ± 1.41 |
0.493 |
14.42 ± 1.99 |
NA |
14.25 ± 1.06 |
0.772 |
|
5 |
15 ± 2.2 |
NA |
17 ± 0.0 |
0.117 |
14.94 ± 2.21 |
NA |
17 ± 0.0 |
0.166 |
|
6 |
17.11 ± 4.84 |
18 ± 0.0 |
NA |
0.271 |
16.5 ± 1.34 |
18 ± 0.0 |
NA |
0.243 |
|
7 |
17.3 ± 1.69 |
NA |
NA |
NA |
17.36 ± 1.65 |
NA |
NA |
NA |
|
8 |
18.94 ± 2.54 |
NA |
NA |
NA |
18.94 ± 2.55 |
NA |
NA |
NA |
|
9 |
19.07 ± 2.51 |
NA |
NA |
NA |
19.12 ± 2.53 |
NA |
NA |
NA |
|
10 |
19.93 ± 2.04 |
18 ± 0.0 |
NA |
0.168 |
19.79 ± 2.39 |
18 ± 0.0 |
NA |
0.202 |
|
11 |
21.54 ± 1.85 |
NA |
NA |
NA |
21.46 ± 1.72 |
NA |
NA |
NA |
|
12 |
22.28 ± 2.67 |
23.9 ± 0.0 |
24 ± 0.0 |
0.386 |
22.77 ± 1.56 |
24.05 ± 0.0 |
24 ± 0.0 |
0.281 |
|
13 |
22.92 ± 1.78 |
24.4 ± 2.59 |
NA |
0.354 |
22.95 ± 1.75 |
24.47 ± 3.16 |
NA |
0.354 |
|
14 |
23.98 ± 1.9 |
NA |
24.73 ± 0 |
0.914 |
23.97 ± 1.74 |
NA |
25.13 ± 0.0 |
0.329 |
|
15 |
25.29 ± 1.07 |
NA |
26.2 ± 0 |
0.272 |
25.15 ± 1 |
NA |
25.97 ± 0.0 |
0.264 |
|
16 |
24.63 ± 1.49 |
NA |
27.33 ± 1.15 |
0.029 |
24.67 ± 1.53 |
NA |
27.33 ± 1.15 |
0.029 |
|
17 |
24.26 ± 1.98 |
26 ± 0.0 |
NA |
0.480 |
24.34 ± 2.03 |
26 ± 0.0 |
NA |
0.480 |
|
18 |
NA |
NA |
28.1 ± 0.0 |
NA |
NA |
NA |
27.9 ± 0.0 |
NA |
Abbreviations: BMI, body mass index; NA, data not available; SD, standard deviation.
a Kruskal–Wallis test.
The mean length of the ulna according to hand dominance in different age groups is shown in [Table 6]. It also shows that the length of the ulna was not affected by hand dominance (p = 0.796; [Table 6]; [Fig. 4]). The measurement of ICC showed excellent to good inter-observer agreement reliability (Inter-class correlation coefficient for right (0.85, 95% CI–0.66–0.99, p– > 0.05) and left (0.70, 95% CI 0.47–0.99, p– > 0.05) and reliability between different centres (Intra –class correlation coefficient for right (0.91, 95% CI–0.90–0.92, p– > 0.05) and left (0.80, 95% CI 0.77–0.82, p– > 0.05) respectively.
|
Age (y) |
Mean ulnar length (cm) |
p-Value[a] |
|
|---|---|---|---|
|
Hand dominance |
|||
|
Dominant hand: 993 right and 24 left |
Nondominant hand: 993 left and 24 right |
||
|
Mean ± SD |
Mean ± SD |
||
|
1 |
10.18 ± 2.78 |
10.34 ± 3.76 |
0.976 |
|
2 |
12.30 ± 2.67 |
12.29 ± 3.27 |
0.903 |
|
3 |
12.89 ± 1.64 |
12.91 ± 1.70 |
0.910 |
|
4 |
14.41 ± 1.94 |
14.53 ± 2.33 |
0.889 |
|
5 |
15.04 ± 2.14 |
15.06 ± 2.14 |
0.969 |
|
6 |
16.99 ± 4.81 |
16.88 ± 4.12 |
0.888 |
|
7 |
17.40 ± 1.38 |
17.36 1.40 |
0.917 |
|
8 |
19.22 ± 1.64 |
19.19 ± 1.65 |
0.903 |
|
9 |
19.42 ± 1.84 |
19.36 ± 1.84 |
0.823 |
|
10 |
20.04 ± 2.42 |
19.76 ± 2.47 |
0.930 |
|
11 |
21.99 ± 1.72 |
21.94 ± 1.72 |
0.737 |
|
12 |
22.69 ± 1.86 |
22.52 ± 2.32 |
0.858 |
|
13 |
22.96 ± 2.34 |
22.88 ± 2.29 |
0.825 |
|
14 |
24.31 ± 1.89 |
24.20 ± 1.91 |
0.817 |
|
15 |
25.76 ± 2.04 |
25.74 ± 2.04 |
0.953 |
|
16 |
25.65 ± 2.13 |
25.75 ± 1.89 |
0.992 |
|
17 |
25.53 ± 2.11 |
25.38 ± 2.00 |
0.733 |
|
18 |
27.06 ± 1.38 |
26.91 ± 1.41 |
0.796 |
a Kruskal–Wallis test.
On multiple regression analysis, the geographical zone, gender, and age were statistically significant, but BMI and hand dominance were not significant for both upper limbs ([Table 7]; [Fig. 5]).
Abbreviations: BMI, body mass index; CI, confidence interval; SE, standard error; VIF, variance inflation factor.
Note: Multiple regression model of the right (r = 0.88) and left hands (r = 0.75) with demographic variables was strongly positive on both sides.
Acceptable tolerance range is <0.10 and VIF <10.
The ulnar length-to-height ratio of the children was assessed and out of 2,100 ulnae (n = 1,050), 2,032 ulnae (n = 1,016) fell between 0.1 and 0.2. The remaining 34 patients had a ratio of less than 0.10 and greater than 0.20 ([Table 8]).
Abbreviation: SD, standard deviation.
#
Discussion
Our multicentric study provides normative data on the percutaneous length of the ulna in the Indian pediatric population across different ages, genders, BMI, and geographical zones. To our knowledge, this is the first study to report normative data on ulnar length in the pediatric Indian population. Such data are essential for describing the natural history of disease, developing standards of care, establishing illness classifications, and evaluating the clinical significance of therapeutic interventions.[8] [9] [10]
There are no widely accepted objective assessment tools for estimation after surgical reconstruction of congenital and traumatic forearm abnormalities. Normative data of the forearm act as the gold standard reference for evaluating the clinical outcome of therapeutic interventions, comparison of treatment, and follow-up with that of normative individuals matched for their age, gender, and different congenital and traumatic anomalies of the hand and forearm.[9] [11] [12] Randomized clinical trials (RCTs) can also establish the statistical significance of treatment efficacy and effectiveness of outcomes at “beyond-chance” levels. However, conducting RCT for surgical treatment may not be feasible or ethical.[13]
The utility of normative data for ulnar length would be in congenital radial dysplasia and fractures involving the physis of the distal forearm. Radial longitudinal deficiency (RLD) or radial club hand account for 25 to 33% of all upper limb deficiencies, with an incidence that varies from 1 in 30,000 to 100,000 live births in different studies. The prevalence has been reported to be higher in boys, at a ratio of 3:2, and they are bilateral in 38 to 58% of cases.[14] [15] Different surgeries have been described for correction of radial club hand such as “centralization” or “radialization” of the wrist.[16] [17] A study by Bhat et al showed at long-term follow-up after radialization that the length of the affected ulna was 56% of the length of the normal ulna.[18] Thatte and Mehta found that the mean ulnar length was 69 and 62%, respectively, of the contralateral ulna at 5 years of follow-up in 21 cases of unilateral and bilateral RLD operated by distraction, radialization, and Evan's bilobed flap.[19] Other surgical options include cubitocarpal arthrodesis and transfer of the second metacarpophalangeal joint. However, the results of these surgeries were variable with poor growth of the ulna and issue of the limb length discrepancy at skeletal maturity. The nonsurgically treated group attained 64% of normal ulnar length, whereas the centralization group attained 48 to 58% of normal ulnar length.[11] Therefore, the normative data of the ulnar length are very useful in determining the natural history of RLD and comparison of results of different techniques. This is especially true in a treated cohort with bilateral radial dysplasia where an opposite limb is not available for comparison.
Fractures involving the physis of the distal forearm are very common in children, which may lead to premature physeal arrest in approximately 55% cases and significant growth disturbance. Growth disturbance can occur in the forms of growth arrest or overgrowth.[20] [21] Thus, the availability of normative data on ulnar length is important for understanding the natural history and complications that may result from an injury commonly encountered in orthopaedic practice. In cases of unilateral involvement, hand function can be compared with the normal side as the human body is bilaterally symmetrical. However, asymmetries may be found for an individual, making it impractical to compare with the contralateral limb, again emphasizing the utility of the normative data.[22] Another utility of normative data is that normal variants can cause significant anxiety to parents, who present the child for assessment and seek reassurance. Knowing normal variants can avoid unnecessary referrals, which resolve spontaneously with normal growth and development without intervention.[23]
The growth of limbs is dependent on the age, sex, and race of the individual. The length of the ulna increases with age, and there is a strong correlation between the length of the ulna and age; however, the extent of lengthening is still unclear.[24] In our study, we found a linear growth of the ulna with increasing age. Asymmetries in the length of the long bones due to hand preference can be attributed to mechanical stress and strain or to genetic or hormonal factors. However, the effect of hand preference is negated because individuals frequently employ both hands to perform many tasks.[25] Our study also found no difference in growth rate in both hands. The final length of the long bones is determined by estrogen as it is responsible for fusion of their epiphyseal growth plates. Hence, earlier maturation may lead to premature termination of long bone growth, resulting in a shorter length of the long bones in female children.[26] Our study also showed that the ulnar length was greater in males; however, the difference was negated at maturity.
Ulnar length can be used as a surrogate marker for estimation of height, gender, and pulmonary function in children. There are many studies that showed definite a correlation between ulnar length and height and gender of the individual.[7] [27] [28] We have also correlated the ulna length with height of children and data showed that ulna length and height ratio falls between 0.10–0.20 in ~97% children. Therefore ratio between 0.10–0.20, is within the normal range for pediatric age group and we termed this as Indian ratio.
The ulna is a subcutaneous bone that is easily accessible. This makes the ulna a perfect anatomical structure for taking anthropometric measurements in a large population. We used a calibrated measuring tape to estimate the ulnar length. Alternative methods for measurement that can be used include digital sliding calipers, forearm X-ray, xerox copies of the forearm, and segmometer using dual-energy X-ray absorptiometry (DXA). However, a bias was observed with segmometer measurements, which overestimate the DXA measurements. This is likely due to the inclusion of soft tissue when using a segmometer as opposed to a direct bone measurement.[29] [30]
The specific limitation of the study is the nonuniform sample size leading to potential bias due to sampling error. The major drawbacks with normative data are difficulty in determining to what extent data from a population could be applied to determine individual normative data.[31] In general, the normative data should be applied with caution in clinical decision-making and should be used with correlated variables, and mainly when the “extreme values” correspond with poor performance or with symptoms.[32] Furthermore, the normative values and ranges should be interpreted in the context of limitations associated with instrument and techniques and limitations associated with using each technique used for collecting normative data. We have used a calibrated measuring tape to avoid this pitfall of measuring instrument. Regardless of the limitations, the clinical norms are useful guidelines for clinical practice. The strength of the study includes power and appropriate sample size, appropriateness of demographic characteristics, and use of appropriate instrument for measurement.
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Conclusion
This multicentric study provides normative data on percutaneous length of the ulna in the Indian pediatric population. Gradual lengthening of ulna was seen in all children with increasing age however; after 14 years though the ulna length continues to grow further but did not achieve statistical significance. The length of ulna was significantly more in males, obese and in South Indians. However, except for age, other factors become insignificant at maturity. These data may serve as a guide to predict response to treatment and compare different treatment functional outcomes of congenital, traumatic, neoplastic, and metabolic abnormalities affecting the forearm bones.
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Conflict of Interest
None declared.
Authors' Contributions
M.R.T. contributed to conceptualization, data collection, data analysis, and manuscript writing and editing. P.A. and A.B. contributed to data collection, data analysis, and manuscript writing and editing. P.U.F.B., B.G., M.P., H.R.S., O.K., and A.D. contributed to data collection, data analysis, and manuscript writing. M.S., R.B., and R.A.S contributed to data collection and data analysis. J.S.D. contributed to data analysis. D.S. contributed to manuscript writing and editing.
Ethical Approval
This study was approved by the institutional review board. All centers involved in study obtained institutional ethics committee clearance.
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References
- 1 Abe M, Shirai H, Okamoto M, Onomura T. Lengthening of the forearm by callus distraction. J Hand Surg [Br] 1996; 21 (02) 151-163
- 2 Demir B, Gursu S, Ozturk K, Yildirim T, Konya MN, Er T. Single-stage treatment of complete dislocation of radial head and forearm deformity using distraction osteogenesis in paediatric patients having multiple cartilaginous exostosis. Arch Orthop Trauma Surg 2011; 131 (09) 1195-1201
- 3 Goldfarb CA, Gee AO, Heinze LK, Manske PR. Normative values for thumb length, girth, and width in the pediatric population. J Hand Surg Am 2005; 30 (05) 1004-1008
- 4 Gul H, Mansor Nizami S, Khan MA. Estimation of body stature using the percutaneous length of ulna of an individual. Cureus 2020; 12 (01) e6599
- 5 Gauld LM, Kappers J, Carlin JB, Robertson CF. Prediction of childhood pulmonary function using ulna length. Am J Respir Crit Care Med 2003; 168 (07) 804-809
- 6 Illayperuma I, Nanayakkara G, Palahepitiya N. A model for the estimation of personal stature from the length of forearm. Int J Morphol 2010; 28 (04) 1081-1086
- 7 Bonell A, Huyen NN, Phu VD, Wertheim H, Nadjm B. Determining the predictive equation for height from ulnar length in the Vietnamese population. Asia Pac J Clin Nutr 2017; 26 (06) 982-986
- 8 O'Connor PJ. Normative data: their definition, interpretation, and importance for primary care physicians. Fam Med 1990; 22 (04) 307-311
- 9 Schmidt S, Pardo Y. Normative data. In: Michalos AC. ed. Encyclopedia of Quality of Life and Well-Being Research. Dordrecht: Springer Netherlands; 2014: 4375-4379
- 10 Kendall PC, Sheldrick RC. Normative data for normative comparisons. J Consult Clin Psychol 2000; 68 (05) 767-773
- 11 Sestero AM, Van Heest A, Agel J. Ulnar growth patterns in radial longitudinal deficiency. J Hand Surg Am 2006; 31 (06) 960-967
- 12 Cannata G, De Maio F, Mancini F, Ippolito E. Physeal fractures of the distal radius and ulna: long-term prognosis. J Orthop Trauma 2003; 17 (03) 172-179 , discussion 179–180
- 13 Kendall PC, Flannery-Shroeder EC, Ford JD. Therapy outcome research methods. In: Kendall PC, Butcher JN, Holmbeck GN. eds. Handbook of Research Methods in Clinical Psychology. New York, NY: Wiley; 1999: 330-363
- 14 Pakkasjärvi N, Koskimies E, Ritvanen A, Nietosvaara Y, Mäkitie O. Characteristics and associated anomalies in radial ray deficiencies in Finland: a population-based study. Am J Med Genet A 2013; 161A (02) 261-267
- 15 Shin YH, Baek GH, Kim Y-J, Kim M-J, Kim JK. Epidemiology of congenital upper limb anomalies in Korea: a nationwide population-based study. PLoS One 2021; 16 (03) e0248105
- 16 Wall LB, Kim DJ, Cogsil T, Goldfarb CA. Treatment of radial longitudinal deficiency: an international survey. J Hand Surg Am 2021; 46 (03) 241.e1-241.e11
- 17 Buck-Gramcko D. Radialization for radial club hand. Tech Hand Up Extrem Surg 1999; 3 (01) 2-12
- 18 Bhat AK, Narayanakurup JK, Acharya AM, Kumar B. Outcomes of radialization for radial longitudinal deficiency: 20 limbs with minimum 5-year follow-up. J Hand Surg Eur Vol 2019; 44 (03) 304-309
- 19 Thatte MR, Mehta R. Treatment of radial dysplasia by a combination of distraction, radialisation and a bilobed flap: the results at 5-year follow-up. J Hand Surg Eur Vol 2008; 33 (05) 616-621
- 20 Stilli S, Magnani M, Lampasi M, Antonioli D, Bettuzzi C, Donzelli O. Remodelling and overgrowth after conservative treatment for femoral and tibial shaft fractures in children. Chir Organi Mov 2008; 91 (01) 13-19
- 21 Golz RJ, Grogan DP, Greene TL, Belsole RJ, Ogden JA. Distal ulnar physeal injury. J Pediatr Orthop 1991; 11 (03) 318-326
- 22 Pierre MA, Zurakowski D, Nazarian A, Hauser-Kara DA, Snyder BD. Assessment of the bilateral asymmetry of human femurs based on physical, densitometric, and structural rigidity characteristics. J Biomech 2010; 43 (11) 2228-2236
- 23 Molony D, Hefferman G, Dodds M, McCormack D. Normal variants in the paediatric orthopaedic population. Ir Med J 2006; 99 (01) 13-14
- 24 Wu C, Wang D, Mo Y, Zhang Z, Ning B. Characteristics of the length of the radius and ulna in children. Front Pediatr 2022; 10: 737823
- 25 Kumar S, Voracek M, Singh M. The effects of hand preference and sex on right-left asymmetry in dorsal digit lengths among adults and children. Early Hum Dev 2021; 153: 105293
- 26 Nowak-Szczepanska N, Koziel S. Sexual dimorphism in growth in the relative length of the forearm and relative knee height during adolescence. Am J Phys Anthropol 2016; 161 (02) 276-282
- 27 Pandey A, Radhika PM, Shailaja S. Estimation of human stature from length of ulna in Indian population. Int J Anat Res 2017; 5 (01) 3350-3353
- 28 Banyeh M, Abdulai AR, Shittu SO, Osei EE, Poku EO, Komla AA. Sex and height estimation using percutaneous ulna and tibia length in a Ghanaian population: new data and a test of published equations. Forensic Sci Int Rep 2022; 6: 100284
- 29 Weidauer L, Wey H, Slater H, Moyer-Mileur L, Specker B. Estimation of length or height in infants and young children using ulnar and lower leg length with dual-energy X-ray absorptiometry validation. Dev Med Child Neurol 2014; 56 (10) 995-1000
- 30 Liu L, Liu C, Rong YB, Bai F, Chen SL. Radial pronation angle: a novel radiological evaluation index of congenital proximal radioulnar synostosis. Ann Plast Surg 2020; 84 (5S, suppl 3): S196-S201
- 31 Scheiman M, Herzberg H, Frantz K, Margolies M. A normative study of step vergence in elementary schoolchildren. J Am Optom Assoc 1989; 60 (04) 276-280
- 32 Morgan MW. Analysis of clinical data. Am J Optom Arch Am Acad Optom 1944; 21: 477-491
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Publication History
Article published online:
05 August 2024
© 2024. Association of Plastic Surgeons of India. This is an open access article published by Thieme under the terms of the Creative Commons Attribution-NonDerivative-NonCommercial License, permitting copying and reproduction so long as the original work is given appropriate credit. Contents may not be used for commercial purposes, or adapted, remixed, transformed or built upon. (https://creativecommons.org/licenses/by-nc-nd/4.0/)
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References
- 1 Abe M, Shirai H, Okamoto M, Onomura T. Lengthening of the forearm by callus distraction. J Hand Surg [Br] 1996; 21 (02) 151-163
- 2 Demir B, Gursu S, Ozturk K, Yildirim T, Konya MN, Er T. Single-stage treatment of complete dislocation of radial head and forearm deformity using distraction osteogenesis in paediatric patients having multiple cartilaginous exostosis. Arch Orthop Trauma Surg 2011; 131 (09) 1195-1201
- 3 Goldfarb CA, Gee AO, Heinze LK, Manske PR. Normative values for thumb length, girth, and width in the pediatric population. J Hand Surg Am 2005; 30 (05) 1004-1008
- 4 Gul H, Mansor Nizami S, Khan MA. Estimation of body stature using the percutaneous length of ulna of an individual. Cureus 2020; 12 (01) e6599
- 5 Gauld LM, Kappers J, Carlin JB, Robertson CF. Prediction of childhood pulmonary function using ulna length. Am J Respir Crit Care Med 2003; 168 (07) 804-809
- 6 Illayperuma I, Nanayakkara G, Palahepitiya N. A model for the estimation of personal stature from the length of forearm. Int J Morphol 2010; 28 (04) 1081-1086
- 7 Bonell A, Huyen NN, Phu VD, Wertheim H, Nadjm B. Determining the predictive equation for height from ulnar length in the Vietnamese population. Asia Pac J Clin Nutr 2017; 26 (06) 982-986
- 8 O'Connor PJ. Normative data: their definition, interpretation, and importance for primary care physicians. Fam Med 1990; 22 (04) 307-311
- 9 Schmidt S, Pardo Y. Normative data. In: Michalos AC. ed. Encyclopedia of Quality of Life and Well-Being Research. Dordrecht: Springer Netherlands; 2014: 4375-4379
- 10 Kendall PC, Sheldrick RC. Normative data for normative comparisons. J Consult Clin Psychol 2000; 68 (05) 767-773
- 11 Sestero AM, Van Heest A, Agel J. Ulnar growth patterns in radial longitudinal deficiency. J Hand Surg Am 2006; 31 (06) 960-967
- 12 Cannata G, De Maio F, Mancini F, Ippolito E. Physeal fractures of the distal radius and ulna: long-term prognosis. J Orthop Trauma 2003; 17 (03) 172-179 , discussion 179–180
- 13 Kendall PC, Flannery-Shroeder EC, Ford JD. Therapy outcome research methods. In: Kendall PC, Butcher JN, Holmbeck GN. eds. Handbook of Research Methods in Clinical Psychology. New York, NY: Wiley; 1999: 330-363
- 14 Pakkasjärvi N, Koskimies E, Ritvanen A, Nietosvaara Y, Mäkitie O. Characteristics and associated anomalies in radial ray deficiencies in Finland: a population-based study. Am J Med Genet A 2013; 161A (02) 261-267
- 15 Shin YH, Baek GH, Kim Y-J, Kim M-J, Kim JK. Epidemiology of congenital upper limb anomalies in Korea: a nationwide population-based study. PLoS One 2021; 16 (03) e0248105
- 16 Wall LB, Kim DJ, Cogsil T, Goldfarb CA. Treatment of radial longitudinal deficiency: an international survey. J Hand Surg Am 2021; 46 (03) 241.e1-241.e11
- 17 Buck-Gramcko D. Radialization for radial club hand. Tech Hand Up Extrem Surg 1999; 3 (01) 2-12
- 18 Bhat AK, Narayanakurup JK, Acharya AM, Kumar B. Outcomes of radialization for radial longitudinal deficiency: 20 limbs with minimum 5-year follow-up. J Hand Surg Eur Vol 2019; 44 (03) 304-309
- 19 Thatte MR, Mehta R. Treatment of radial dysplasia by a combination of distraction, radialisation and a bilobed flap: the results at 5-year follow-up. J Hand Surg Eur Vol 2008; 33 (05) 616-621
- 20 Stilli S, Magnani M, Lampasi M, Antonioli D, Bettuzzi C, Donzelli O. Remodelling and overgrowth after conservative treatment for femoral and tibial shaft fractures in children. Chir Organi Mov 2008; 91 (01) 13-19
- 21 Golz RJ, Grogan DP, Greene TL, Belsole RJ, Ogden JA. Distal ulnar physeal injury. J Pediatr Orthop 1991; 11 (03) 318-326
- 22 Pierre MA, Zurakowski D, Nazarian A, Hauser-Kara DA, Snyder BD. Assessment of the bilateral asymmetry of human femurs based on physical, densitometric, and structural rigidity characteristics. J Biomech 2010; 43 (11) 2228-2236
- 23 Molony D, Hefferman G, Dodds M, McCormack D. Normal variants in the paediatric orthopaedic population. Ir Med J 2006; 99 (01) 13-14
- 24 Wu C, Wang D, Mo Y, Zhang Z, Ning B. Characteristics of the length of the radius and ulna in children. Front Pediatr 2022; 10: 737823
- 25 Kumar S, Voracek M, Singh M. The effects of hand preference and sex on right-left asymmetry in dorsal digit lengths among adults and children. Early Hum Dev 2021; 153: 105293
- 26 Nowak-Szczepanska N, Koziel S. Sexual dimorphism in growth in the relative length of the forearm and relative knee height during adolescence. Am J Phys Anthropol 2016; 161 (02) 276-282
- 27 Pandey A, Radhika PM, Shailaja S. Estimation of human stature from length of ulna in Indian population. Int J Anat Res 2017; 5 (01) 3350-3353
- 28 Banyeh M, Abdulai AR, Shittu SO, Osei EE, Poku EO, Komla AA. Sex and height estimation using percutaneous ulna and tibia length in a Ghanaian population: new data and a test of published equations. Forensic Sci Int Rep 2022; 6: 100284
- 29 Weidauer L, Wey H, Slater H, Moyer-Mileur L, Specker B. Estimation of length or height in infants and young children using ulnar and lower leg length with dual-energy X-ray absorptiometry validation. Dev Med Child Neurol 2014; 56 (10) 995-1000
- 30 Liu L, Liu C, Rong YB, Bai F, Chen SL. Radial pronation angle: a novel radiological evaluation index of congenital proximal radioulnar synostosis. Ann Plast Surg 2020; 84 (5S, suppl 3): S196-S201
- 31 Scheiman M, Herzberg H, Frantz K, Margolies M. A normative study of step vergence in elementary schoolchildren. J Am Optom Assoc 1989; 60 (04) 276-280
- 32 Morgan MW. Analysis of clinical data. Am J Optom Arch Am Acad Optom 1944; 21: 477-491