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## Jornal de Pediatria

*Print version* ISSN 0021-7557

### J. Pediatr. (Rio J.) vol.82 no.4 Porto Alegre July/Aug. 2006

#### http://dx.doi.org/10.2223/JPED.1502

**ORIGINAL ARTICLE **

**Body mass index cutoff
points for evaluation of nutritional status in Brazilian children and adolescents**

**Wolney L. Conde ^{I}; Carlos A. Monteiro^{II}**

^{I}Professor Doutor, Universidade de
São Paulo (USP), São Paulo, SP, Brasil

^{II}Professor titular, USP, São Paulo, SP, Brasil

**ABSTRACT**

**OBJECTIVE:** To delineate a classification
system, comprising reference curves and cutoff points, based on the distribution
of body mass index (BMI) across a national reference population and designed
for the assessment of the nutritional status of Brazilian children and adolescents.

**METHODS:** Data from 13,279 males and 12,823 females aged from 2 to 19
years, extracted from the National Nutrition and Health Survey dataset (1989),
were used to construct a reference curve. The LMS method was employed to calculate
the BMI curve parameters and polynomial functions were used to model these parameters
against age. The cutoff values for classifying nutritional status as underweight,
overweight and obese were expressed as centiles and BMI values equivalent to
17.5, 25 and 30 kg/m^{2} at 20 years, respectively.

**RESULTS:** Values for the L, M and S parameters were tabulated at 6-month
intervals for each sex. Using these values, a graph was plotted with nine BMI
distribution reference centiles. Cutoff values were presented that are equivalent
to BMIs of 17.5, 25 and 30 kg/m^{2} at the start of adulthood.

**CONCLUSIONS:** The classification system presented here can be used for
clinical and epidemiological assessments, it is methodologically similar to
the majority of national curves that have been presented to date and, furthermore,
it offers a definition of underweight.

**Keywords:** Reference standards, nutritional
status, children, adolescents, BMI.

**Introduction**

The use of anthropometric measurements for the evaluation of nutritional status has become, albeit with limitations, the most practical and lowest cost means of analyzing individuals and populations, whether for clinical reasons, for screening projects or for monitoring tendencies.

An anthropometric reference standard or curve
is a summarized representation of the distribution of a given anthropometric
measurement according to a co-variable (usually age) and for each sex.^{1}
Reference curves represent a "healthy empirical model" and serve both for classification
(comparing against the reference group) and for diagnosis (to separate healthy
form unhealthy individuals) of the nutritional status of an individual or population.

Historically, the basis of anthropometric diagnosis
of childhood nutritional status has oscillated between epidemiological and statistical
foundations. Included in the initial classification systems are those proposed
by Gomez, McLaren and Waterlow. These proposals were debated on the basis of
indicators and outcomes selected to describe and classify childhood nutritional
status.^{2} Waterlow was the first of these to propose a classification
system that was effectively probabilistic, i.e. statistical - to deal with the
classification of nutritional status in children. This proposal was adopted
by the WHO in 1975^{3} and, since then, has predominated in the diagnosis
of childhood nutritional status. Nevertheless, the choice of probabilistic classification
for nutritional status in children contrasts with the classification of nutritional
status in adults based on body mass index (BMI). In the latter case, classification
is based on the no risk of mortality or disease associated with different BMI
ranges, an epidemiological criterion.

The nutritional status of people less than 20
years old has traditionally been classified on the basis of probabilistic criteria.
In 1997, the International Obesity Task Force (IOTF) proposed that nutritional
status of people under 20 be defined on the basis of outcomes which, in adulthood
would define diagnoses of malnutrition, overweight and obesity and/or on the
basis of alterations to a variety of biochemical indicators that are associated
with chronic diseases in the adult phase.^{4} In 2000, a suite of cutoff
values was published to define overweight and obesity in the 2 to 18 year age
group.^{5}

The use of curves based on BMI for age to define
the nutritional status of children and adolescents offered practical solutions,
but, on the other hand, it has also opened a debate on the use of such curves
to assess the nutritional status of populations made up of growing individuals.
The main points of this debate center on: 1) the universal or specific nature
of body composition, a feature that is reflected in the debate on the adoption
of local or international reference curves;^{6,7} 2) the underlying
principals and properties of a classification system based on BMI for age, which
is reflected in the debate on the use of statistical or epidemiological criteria^{8}
and; 3) the influence of sexual maturation on body composition and the need
to take account or not the stage of sexual maturity of those assessed.^{9,10}

The objective of this paper is to present a reference system based on BMI, for the assessment of the nutritional status of Brazilian children and adolescents including the delineation of a reference curve and the definition of "statistical" and "functional" cutoff points for the diagnosis of malnutrition, overweight and obesity.

**Material and methods **

The dataset employed for delineation of the national
BMI reference curve comes from the National Nutrition and Health Survey (*Pesquisa
Nacional de Saúde e Nutrição*, PNSN) carried out by
the Brazilian Institute of National Statistics and Geography in 1989.^{11}
The rigorous preparation and quality control observed during collection of anthropometric
measurements, in addition to its national representativity (with the exception
of the rural area of the North region), were decisive in the choice of this
database.

In order to determine the adequacy of the PNSN
dataset to the study objectives, the following analysis was performed: the PNSN
data and data from the National Survey on Household Expenses (*Estudo Nacional
de Despesa Familiar*, ENDEF), performed 14.5 years earlier, were standardized
for age and sex according to CDC 2000 reference values for height and weight
and then compared. Secular tendencies of figures for height for age below 2
z-scores and weight for age above 2 z-scores were observed. Over the period
a reduction had occurred in height deficits (-59.5%) and there had been an increase
in overweight (106.5%). However, the frequency of individuals whose weights
for age were above 2 z-scores on the PNSN did not pass the classification's
probability value.

The individuals selected for this study were 2 to 19 years old, with complete data available for sex, age (expressed in months), height (in cm, to one decimal place) and weight (in kg, to one decimal place). The final sample comprised 13,279 males and 12,823 females, representing 99% of available individuals of each sex.

Values for BMI more than 4 standard deviations from the mean from age and sex were excluded. The unconventional cutoff of ± 4 deviations was chosen to preserve, as far as possible, the heterogeneous nature of the sample.

The method used to compile the Brazilian curves
was basically the same as that used to produce the BMI international standards.^{5}
In essence the LMS method assumes that, for independent data with positive values,
the age-specific Box-Cox transformation can be used to make data normally distributed;
the L values, M and S are *natural cubic splines* with *knots* at
each age interval.^{12} Each sample, male and female, was split into
3-month age groups. This 3-month subdivision was intended to represent the diversity
of growth velocity and to ensure at least 100 individuals in each stratum, which
is considered the minimum required for the LMS method. The L, M and S parameters
were calculated for each stratum. The M parameter expresses the median value
of the observed index within each stratum; the S parameter represents the coefficient
of variation of each stratum and the L parameter the coefficient (Box-Cox) employed
for the mathematical transformation of the BMI figures with the objective of
obtaining normal distribution within each stratum. The value chosen for the
L coefficient is that value whose transformation produces the lowest sum of
the squares of the deviations of the variable. Next the curves for each parameter
were smoothed using polynomials for each sex. Finally, by means of interpolation
based on arithmetic means, monthly distribution values were obtained.

Using these three parameters it is possible to construct a curve for any centile that is required, using the formula:

C_{100a(t)}
= M_{(t)} [1 + L_{(t)}S_{(t)}Z_{a}]^{1/L}_{(t),} |
(1) |

where Z_{a}
is the equivalent normal deviation for the area a;
C_{100a(t)} is the centile corresponding
to Za;* t *is age in months and L_{(t)},
M_{(t)}, S_{(t)} and C_{100a(t)}
indicate the corresponding values for each curve at age* t*.

In order to establish cut off points for the
classification of nutritional status according to statistical criteria, the
formula^{1} used z values equivalent to centiles 85 and 95, recommended
to diagnose overweight and obesity, respectively.^{13,14}

In order to establish cutoff values according
to epidemiological criteria, the final values desired at 20 years were set at
a BMI of 25 kg/m^{2} for overweight and a BMI of 30 kg/m^{2}
for obesity. Applied to the formula (2), these values allow their equivalent
values over previous years to be estimated retrospectively.

Z = [(BMI/M)^{L}
-1]/(LS) |
(2) |

Additional analyses were carried out in the case
of underweight, bearing in mind that the cutoff point traditionally recommended
(18.5 kg/m^{2}) has not proven adequate for this classification on the
international standard.^{5} The selection of a cutoff point (at 20 years)
to define underweight took account of statistical and epidemiological features.
In the case of statistical criteria, the aim was to maintain compatibility with
those statistical criteria usually employed, i.e. the value of -2 z-scores for
defining nutritional deficits. In the case of epidemiological criteria, the
plausibility of diagnosis was foremost, observed according to the following
two features: 1) the expected prevalence - estimated on the basis of frequency
of the z value - cannot be greater than or equal to the observed prevalence
in the populations under study, in order to reduce the number of false-positive
cases and to improve detection of true-negatives; 2) the BMI distribution at
the start of adulthood selected was from a population in the top quartile of
*per capita* income, a social stratum in which it is improbable that nutritional
deficits of a socioeconomic nature will occur. In this group, the third centile
of BMI between 19.5 and 20.4 years is 17.57 kg/m^{2} for males and 17.48
kg/m^{2} for females.

At 20 years, the z = -2 (p = 0.0228) point for
the PNSN population sample was equivalent to BMI values of 17.78 kg/m^{2}
for males and 17.14 kg/m^{2} for females.

On the basis of the assumptions and evidence
described, the curve corresponding to a BMI of 17.5 kg/m^{2} (at 20
years) was selected as the cutoff point to define underweight in the Brazilian
population. In this manner, the use of a single figure for the classification
of nutritional status of adults of both sexes was maintained for the classification
of underweight.

All analyses were performed using the Stata statistical package (version 8).

**Results**

The low percentage of exclusions (1%), whether because of incomplete data or because of biological implausibility (BMI 4 standard deviations above or below average), is indicative of the consistency of data across the age spectrum, and evidence of the quality of the anthropometric measurements in the database that was employed, in addition to preserving the sample's national representativity.

Subdivision of the sample into three-month age groups resulted in a mean of 190 cases (n, minimum of 129 and maximum of 235) for the male sex, and 183 (minimum of 132 and maximum of 229) for the female sex.

Values for the parameters L, M and S for the Brazilian population are presented in six-month intervals by sex in Table 1.

Smoothing the curves for each sex produced the following results: the L curve was analyzed with a 4th degree polynomial for both sexes, the M curves, with a 4th degree polynomial for males an 8th degree polynomial for females, the S curve was adjusted with a 4th degree polynomial for both sexes.

Table 1 contains descriptive parameters of the reference BMI distribution for the Brazilian population aged 2 to 20 years, obtained at the end of the modeling process. Figure 1 presents, for each sex, seven centiles from the reference distribution.

The L values permit the inference of the magnitude and type of adjust needed to normalize BMI within each stratum. The preponderance of negative values indicates that the data employed in the preparation of the standard proposed exhibited asymmetry (skewness) to the right; the relatively small amplitude of the L parameter, in both sexes, is indicative of the low magnitude of the asymmetry that had to be removed. The mean for the L values for both sexes approaches -1. For the age range where one would expect to find peaks in the sexual maturation process (11 to 13 years), the L parameter had a mean of -1.20. The most intense asymmetrical point was in the age range from 6 to 11 years, a period before the start of the collection of phenomena that make up sexual maturation, with L values of -1.36 for males and -1.38 for females.

The mean variance of BMI across the different strata, expressed by the S parameter, was around 10% for each sex, with a small amplitude (from 8 to 14%). In the age range within which one would expect to observe peak sexual maturation (11 to 13 years), the mean for the S parameter was 13.2%.

The path traced by the S curve against age declines from the start point up to 52 months (4.3 years), at which point it begins to follow an ascending trajectory until the point at which sexual maturation would be expected (11 to 13 years). The S values for both sexes reach their highest values at this stage. Next there is a short stabilization period around the highest values. After the phase of sexual maturation, the S curve takes on different characteristics depending on sex. For males, the S curve exhibits a clear reduction in variance, while for females the reduction is not so accentuated and variance remains concentrated around values close to those at the end of the sexual maturation stage.

Table 2
presents the cutoff points for the Brazilian population aged 2 to 20 years,
obtained by applying formula (1), for the classification of underweight (curve
equivalent to BMI of 17.5 kg/m^{2} at 20 years), overweight (curve equivalent
to BMI of 25 kg/m^{2} at 20 years) and obesity (curve equivalent to
BMI of 30 kg/m^{2} at 20 years).

The curves for the centiles traditionally used
as cutoff points for overweight (centile 85) and obesity (centile 95) together
with those for the values based on outcomes at the start of adulthood (25 kg/m^{2}
and 30 kg/m^{2}, respectively) are shown in Figure 2.
For the male sex, the prevalence rates of underweight, overweight and obesity
would be higher than those obtained if, instead of employing cutoffs based on
adult values, the traditional centiles were used to define these diagnoses.
For females, the same "overestimation" would only occur for diagnoses of obesity;
overweight and underweight would be comparably classified whether using the
85th and 3rd centiles or the curves equivalent to 25 kg/m^{2} and 17.5
kg/m^{2}, respectively.

** Discussion**

The debate on the properties of a national, BMI-based system for the classification of nutritional status in children and adolescents can be broken down into 1) appreciation of the adequacy of the sample used to compile the reference curves and 2) appreciation of the criteria selected to identify the nutritional problems that need to be diagnosed.

An analysis of the period 1974/1975 to 1989 and an analysis of the richest quartile of the PNSN sample shows that the database selected was not negatively impacted by secular height and weight tendencies within the selected group.

Two other published studies have used the PNSN
and described the distribution of BMI by age and sex in Brazilian children and
adolescents. The first of these worked with the 10 to 17 year age group, at
annual intervals. The 10th and 90th percentiles were proposed as cutoffs for
diagnosing nutritional deficit and overweight, respectively. The 99th centile
was chosen because, at 18 years, it coincided with 25 kg/m^{2}. The
values were smoothed using movable means.^{15} The second of these papers
used the 0 to 25 year age range, for both sexes. The resulting values were not
subjected to any kind of modeling.^{16}

While there were differences in terms of statistical
procedure, the two studies exhibited similar values for the distribution of
BMI from 10 and 17 years, the age range that is common to both. The essential
difference between the two studies is that, while Sichieri & Allam^{15}
generated their distribution as a national reference for nutritional classification
by BMI, Anjos et al.^{16} explicitly recommend that their distribution
should not be used for nutritional diagnosis.

Modeling of data that change with age and are,
originally, asymmetrical, can be performed using a variety of methods.^{17}
Using the LMS method allows Box-Cox transformation to be performed (which is
efficient at removing asymmetry), and also to independently model the coefficient
of variation, better than standard deviation. Furthermore, the fact that LMS
is the most widely used method for the delineation of BMI reference curves allows
for greater international compatibility between the parameters compiled here
and those of curves from other countries or from international ones. Some exercises
already carried out along these lines have demonstrated that using the international
curve can alter the prevalence of overweight as measured during childhood and
adolescence. The direction of the effect depends on age group and national characteristics.^{18,19}

The decision on which criteria to adopt for the classification of nutritional status in children and adolescents based on their BMI is a subject that is still open, although recently opinion has been coalescing around the option tom use the set of curves obtained by retrogression from the values used to classify the nutritional status of young adults. In the Brazilian context, using the 85th and 95th centiles, rather than adult BMI-based cutoffs, would result in higher numbers of women diagnosed as obese and for men, higher prevalence rates of malnutrition, overweight and obesity. The observation that height continues to increase until close to 20 years in the population used to construct the curve, motivated the choice of this age for BMI outcomes. Any possible option for a classification system based on adult outcomes, however, should only be chosen after wider discussion, which should take account of the aspect of classifying nutritional deficits.

The proposal made here of using a BMI of 17.5
kg/m^{2} as a cutoff point for nutritional deficit among children and
adolescents, however, requires further analysis and wider discussion before
possibly being adopted.

The process of sexual maturation, whose progress includes modifications to body composition, can be a complicating factor when performing nutritional assessment on the basis of BMI for age. Therefore, analysis of variance within and across generations is the key issue for answering the question of whether or not it is necessary to control for phase of sexual maturity.

Evidence obtained from population studies suggests
that intergenerational variation is smaller than intragenerational. This includes:
1) the small differences observed between countries in terms of median age of
menarche and the reduction in the rhythm of secular tendencies, in particular
when analyzed according to Tanner stages;^{20} 2) indications that,
for the population as a whole, countries such as the USA and Holland do not
currently exhibit the tendency towards reducing age at menarche;^{21,22}
3) in Brazil, the reduction in age at menarche is estimated at 2.4 to 2.7 months
per decade.^{23,24}

Taken together this evidence allows for the assumption that, in the case of Brazil, the impact of intergenerational variation (including variations within and between individuals) should not distort the curves presented here.

**References**

1. Cole TJ. The use and construction of anthropometric growth reference standards. Nutr Res Rev. 1993;6:19-50. [ Links ]

2. Zerfas AJ, Jelliffe DB, Jellife EFP. Epidemiology and nutrition. In: Falkner F, Tanner JM, editors. Human growth - a comprehensive treatise. New York: Plenum Press; 1986. p. 475-500. [ Links ]

3. Waterlow JC, Buzina R, Keller W, Lane JM, Nichaman MZ, Tanner JM. The presentation and use of height and weight data for comparing the nutritional status of groups of children under the age of 10 years. Bull World Health Organ. 1977;55:489-98. [ Links ]

4. Bellizzi MC, Dietz WH. Workshop on childhood obesity: summary of the discussion. Am J Clin Nutr. 1999;70:173S-5S. [ Links ]

5. Cole TJ, Bellizzi MC, Flegal KM, Dietz WH. Establishing a standard definition for child overweight and obesity worldwide: international survey. BMJ. 2000;320:1240-3. [ Links ]

6. Piers LS, Rowley KG, Soares MJ, O'Dea K. Relation of adiposity and body fat distribution to body mass index in Australians of Aboriginal and European ancestry. Eur J Clin Nutr. 2003;57:956-63. [ Links ]

7. Reilly JJ. Assessment of childhood obesity: national reference data or international approach? Obes Res. 2002;10:838-40. [ Links ]

8. Cole TJ , Roede MJ. Centiles of body mass index for Dutch children aged 0-20 years in 1980 - a baseline to assess recent trends in obesity. Ann Hum Biol. 1999;26:303-8 [ Links ]

9. Wang Y. Is obesity associated with early sexual maturation? A comparison of the association in American boys versus girls. Pediatrics. 2002;110:903-10. [ Links ]

10. Bini V, Celi F, Berioli MG, Bacosi ML, Stella P, Giglio P, et al. Body mass index in children and adolescents according to age and pubertal stage. Eur J Clin Nutr. 2000;54:214-8. [ Links ]

11. Instituto Brasileiro de Geografia e Estatística, Fundo das Nações Unidas para a Infância. Perfil estatístico de crianças e mães no Brasil: aspectos de saúde e nutrição de crianças no Brasil. Rio de Janeiro: IBGE; 1992. [ Links ]

12. Cole TJ, Freeman JV, Preece MA. British 1990 growth reference centiles for weight, height, body mass index and head circumference fitted by maximum penalized likelihood. Stat Med. 1998;17:407-29. [ Links ]

13. World Health Organization. Physical status: the use and interpretation of anthropometry. Geneva: WHO; 1995. WHO Technical Report Series nº 854. [ Links ]

14. Barlow SE, Dietz WH. Management of child and adolescent obesity: summary and recommendations based on reports from pediatricians, pediatric nurse practitioners and registered dietitians. Pediatrics. 2002;110:236-8. [ Links ]

15. Sichieri R, Allam VLC. Avaliação do estado nutricional de adolescentes brasileiros através do índice de massa corporal. J Pediatr (Rio J). 1996;72:80-4. [ Links ]

16. Anjos LA, Veiga GV, Castro IRR. Distribuição dos valores do índice de massa corporal da população brasileira até 25 anos. Rev Panam Salud Publica. 1998;3:164-73. [ Links ]

17. Wright EM, Royston P. Simplified estimation of age-specific reference intervals for skewed data. Stat Med. 1997;16:2785-803. [ Links ]

18. Wang Y, Wang JQ. A comparison of international references for the assessment of child and adolescent overweight and obesity in different populations. Eur J Clin Nutr. 2002;56:973-82. [ Links ]

19. Chinn S, Rona RJ. International definitions of overweight and obesity for children: a lasting solution? Ann Hum Biol. 2002;29:306-13. [ Links ]

20. Lee PA, Guo SS, Kulin HE. Age of puberty: data from the United States of America. APMIS. 2001;109:81-8. [ Links ]

21. Chumlea WC, Schubert CM, Roche AF, Kulin HE, Lee PA, Himes JH, et al. Age at menarche and racial comparisons in US girls. Pediatrics. 2003;111:110-3. [ Links ]

22. Mul D, Fredriks AM, van Buuren S, Oostdijk W, Verloove-Vanhorick SP, Wit JM. Pubertal development in the Netherlands 1965-1997. Pediatr Res. 2001;50:479-86. [ Links ]

23. Kac G, Auxiliadora de Santa Cruz Coel, Velasquez-Melendez G. Secular trend in age at menarche for women born between 1920 and 1979 in Rio de Janeiro, Brazil. Ann Hum Biol. 2000;27:423-8. [ Links ]

24. Junqueira Do Lago M, Faerstein E, De Souza Lopes C, Werneck GL; Pro-Saude Study (Rio de Janeiro, Brazil). Family socio-economic background modified secular trends in age at menarche: evidence from the Pro-Saude Study (Rio de Janeiro, Brazil). Ann Hum Biol. 2003;30:347-52. [ Links ]

**Correspondence:**

Wolney Conde

Av. Dr. Arnaldo, 715, Departamento de Nutrição

CEP 01246-904 - São Paulo, SP - Brazil

Tel./Fax: +55 (11) 3066.7705

E-mail: wolney@usp.br

Manuscript received Sep 27 2005, accepted for publication Apr 29 2006.