Body Mass Index, Cigarette Smoking, and Alcohol Consumption and Cancers of the Oral Cavity, Pharynx, and Larynx: Modeling Odds Ratios in Pooled Case-Control Data

study-specific results, their findings should be interpreted with caution

An examination of male and female odds ratios by BMI, cigarette smoking, and alcohol consumption for cancers of the oral cavity, pharynx, and larynx in pooled data from 15 case-control studies

Greater tobacco smoking and alcohol consumption and lower body mass index (BMI) increase odds ratios (OR) for oral cavity, oropharyngeal, hypopharyngeal, and laryngeal cancers; however, there are no comprehensive sex-specific comparisons of ORs for these factors. We analyzed 2,441 oral cavity (925 women and 1,516 men), 2,297 oropharynx (564 women and 1,733 men), 508 hypopharynx (96 women and 412 men), and 1,740 larynx (237 women and 1,503 men) cases from the INHANCE consortium of 15 head and neck cancer case-control studies. Controls numbered from 7,604 to 13,829 subjects, depending on analysis. Analyses fitted linear-exponential excess ORs models. ORs were increased in underweight (< 18.5 BMI) relative to normal weight (18.5-24.9) and reduced in overweight and obese categories (a parts per thousand yen25 BMI) for all sites and were homogeneous by sex. ORs by smoking and drinking in women compared with men were significantly greater for oropharyngeal cancer (p < 0.01 for both factors), suggestive for hypopharyngeal cancer (p = 0.05 and p = 0.06, respectively), but homogeneous for oral cavity (p = 0.56 and p = 0.64) and laryngeal (p = 0.18 and p = 0.72) cancers. The extent that OR modifications of smoking and drinking by sex for oropharyngeal and, possibly, hypopharyngeal cancers represent true associations, or derive from unmeasured confounders or unobserved sex-related disease subtypes (e.g., human papillomavirus-positive oropharyngeal cancer) remains to be clarified.

Body mass index, cigarette smoking, and alcohol consumption and cancers of the oral cavity, pharynx, and larynx: modeling odds ratios in pooled case-control data.

Odds ratios for head and neck cancer increase with greater cigarette and alcohol use and lower body mass index (BMI; weight (kg)/height(2) (m(2))). Using data from the International Head and Neck Cancer Epidemiology Consortium, the authors conducted a formal analysis of BMI as a modifier of smoking- and alcohol-related effects. Analysis of never and current smokers included 6,333 cases, while analysis of never drinkers and consumers of < or =10 drinks/day included 8,452 cases. There were 8,000 or more controls, depending on the analysis. Odds ratios for all sites increased with lower BMI, greater smoking, and greater drinking. In polytomous regression, odds ratios for BMI (P = 0.65), smoking (P = 0.52), and drinking (P = 0.73) were homogeneous for oral cavity and pharyngeal cancers. Odds ratios for BMI and drinking were greater for oral cavity/pharyngeal cancer (P < 0.01), while smoking odds ratios were greater for laryngeal cancer (P < 0.01). Lower BMI enhanced smoking- and drinking-related odds ratios for oral cavity/pharyngeal cancer (P < 0.01), while BMI did not modify smoking and drinking odds ratios for laryngeal cancer. The increased odds ratios for all sites with low BMI may suggest related carcinogenic mechanisms; however, BMI modification of smoking and drinking odds ratios for cancer of the oral cavity/pharynx but not larynx cancer suggests additional factors specific to oral cavity/pharynx cancer.

An examination of male and female odds ratios by BMI, cigarette smoking, and alcohol consumption for cancers of the oral cavity, pharynx, and larynx in pooled data from 15 case-control studies.

BACKGROUND: Greater tobacco smoking and alcohol consumption and lower body mass index (BMI) increase odds ratios (OR) for oral cavity, oropharyngeal, hypopharyngeal, and laryngeal cancers; however, there are no comprehensive sex-specific comparisons of ORs for these factors. METHODS: We analyzed 2,441 oral cavity (925 women and 1,516 men), 2,297 oropharynx (564 women and 1,733 men), 508 hypopharynx (96 women and 412 men), and 1,740 larynx (237 women and 1,503 men) cases from the INHANCE consortium of 15 head and neck cancer case-control studies. Controls numbered from 7,604 to 13,829 subjects, depending on analysis. Analyses fitted linear-exponential excess ORs models. RESULTS: ORs were increased in underweight (<18.5 BMI) relative to normal weight (18.5-24.9) and reduced in overweight and obese categories (>/=25 BMI) for all sites and were homogeneous by sex. ORs by smoking and drinking in women compared with men were significantly greater for oropharyngeal cancer (p < 0.01 for both factors), suggestive for hypopharyngeal cancer (p = 0.05 and p = 0.06, respectively), but homogeneous for oral cavity (p = 0.56 and p = 0.64) and laryngeal (p = 0.18 and p = 0.72) cancers. CONCLUSIONS: The extent that OR modifications of smoking and drinking by sex for oropharyngeal and, possibly, hypopharyngeal cancers represent true associations, or derive from unmeasured confounders or unobserved sex-related disease subtypes (e.g., human papillomavirus-positive oropharyngeal cancer) remains to be clarified.

Methods to convert continuous outcomes into odds ratios of treatment response and numbers needed to treat: meta-epidemiological study

Clinicians find standardized mean differences (SMDs) calculated from continuous outcomes difficult to interpret. Our objective was to determine the performance of methods in converting SMDs or means to odds ratios of treatment response and numbers needed to treat (NNTs) as more intuitive measures of treatment effect.

A multicentre, retrospective case-control study assessing the role of trabecular bone score (TBS) in menopausal Caucasian women with low areal bone mineral density (BMDa): Analysing the odds of vertebral fracture.

INTRODUCTION: The trabecular bone score (TBS) is a new parameter that is determined from grey level analysis of DXA images. It relies on the mean thickness and volume fraction of trabecular bone microarchitecture. This was a preliminary case-control study to evaluate the potential diagnostic value of TBS, both alone and combined with bone mineral density (BMDa), in the assessment of vertebral fracture. METHODS: Out of a subject pool of 441 Caucasian, postmenopausal women between the ages of 50 and 80 years, we identified 42 women with osteoporosis-related vertebral fractures, and compared them with 126 age-matched women without any fractures (1 case: 3 controls). Primary outcomes were BMDa and TBS. Inter-group comparisons were undertaken using Student's t-tests and Wilcoxon signed ranks tests for parametric and non-parametric data, respectively. Odds ratios for vertebral fracture were calculated for each incremental one standard deviation decrease in BMDa and TBS, and areas under the receiver operating curve (AUC) calculated and sensitivity analysis were conducted to compare BMDa alone, TBS alone, and the combination of BMDa and TBS. Subgroup analyses were performed specifically for women with osteopenia, and for women with T-score-defined osteoporosis. RESULTS: Across all subjects (n=42, 126) weight and body mass index were greater and BMDa and TBS both less in women with fractures. The odds of vertebral fracture were 3.20 (95% CI, 2.01-5.08) for each incremental decrease in TBS, 1.95 (1.34-2.84) for BMDa, and 3.62 (2.32-5.65) for BMDa + TBS combined. The AUC was greater for TBS than for BMDa (0.746 vs. 0.662, p=0.011). At iso-specificity (61.9%) or iso-sensitivity (61.9%) for both BMDa and TBS, TBS + BMDa sensitivity or specificity was 19.1% or 16.7% greater than for either BMDa or TBS alone. Among subjects with osteoporosis (n=11, 40) both BMDa (p=0.0008) and TBS (p=0.0001) were lower in subjects with fractures, and both OR and AUC (p=0.013) for BMDa + TBS were greater than for BMDa alone (OR=4.04 [2.35-6.92] vs. 2.43 [1.49-3.95]; AUC=0.835 [0.755-0.897] vs. 0.718 [0.627-0.797], p=0.013). Among subjects with osteopenia, TBS was lower in women with fractures (p=0.0296), but BMDa was not (p=0.75). Similarly, the OR for TBS was statistically greater than 1.00 (2.82, 1.27-6.26), but not for BMDa (1.12, 0.56-2.22), as was the AUC (p=0.035), but there was no statistical difference in specificity (p=0.357) or sensitivity (p=0.678). CONCLUSIONS: The trabecular bone score warrants further study as to whether it has any clinical application in osteoporosis detection and the evaluation of fracture risk.

Sample size considerations in active-control non-inferiority trials with binary data based on the odds ratio

This paper presents an approximate closed form sample size formula for determining non-inferiority in active-control trials with binary data. We use the odds-ratio as the measure of the relative treatment effect, derive the sample size formula based on the score test and compare it with a second, well-known formula based on the Wald test. Both closed form formulae are compared with simulations based on the likelihood ratio test. Within the range of parameter values investigated, the score test closed form formula is reasonably accurate when non-inferiority margins are based on odds-ratios of about 0.5 or above and when the magnitude of the odds ratio under the alternative hypothesis lies between about 1 and 2.5. The accuracy generally decreases as the odds ratio under the alternative hypothesis moves upwards from 1. As the non-inferiority margin odds ratio decreases from 0.5, the score test closed form formula increasingly overestimates the sample size irrespective of the magnitude of the odds ratio under the alternative hypothesis. The Wald test closed form formula is also reasonably accurate in the cases where the score test closed form formula works well. Outside these scenarios, the Wald test closed form formula can either underestimate or overestimate the sample size, depending on the magnitude of the non-inferiority margin odds ratio and the odds ratio under the alternative hypothesis. Although neither approximation is accurate for all cases, both approaches lead to satisfactory sample size calculation for non-inferiority trials with binary data where the odds ratio is the parameter of interest.

Limitations of the Odds Ratio in Gauging the Performance of a Diagnostic or Prognostic Marker

A marker that is strongly associated with outcome (or disease) is often assumed to be effective for classifying individuals according to their current or future outcome. However, for this to be true, the associated odds ratio must be of a magnitude rarely seen in epidemiological studies. An illustration of the relationship between odds ratios and receiver operating characteristic (ROC) curves shows, for example, that a marker with an odds ratio as high as 3 is in fact a very poor classification tool. If a marker identifies 10 percent of controls as positive (false positives) and has an odds ratio of 3, then it will only correctly identify 25 percent of cases as positive (true positives). Moreover, the authors illustrate that a single measure of association such as an odds ratio does not meaningfully describe a marker’s ability to classify subjects. Appropriate statistical methods for assessing and reporting the classification power of a marker are described. The serious pitfalls of using more traditional methods based on parameters in logistic regression models are illustrated.

Survey regional sobre crescimento e desenvolvimento : relações com maturação, sobrepeso e obesidade, nível socioeconômico e desempenho motor

Universidade Estadual de Campinas . Faculdade de Educação Física

Medidas de associação em estudo transversal com delineamento complexo: razão de chances e razão de prevalência

O objetivo deste estudo foi apresentar e discutir a utilização das medidas de associação: razão de chances e razão de prevalências, em dados obtidos de estudo transversal realizado em 2001-2002, utilizando-se amostra estratificada por conglomerados em dois estágios (n=1.958). As razões de chances e razões de prevalências foram estimadas por meio de regressão logística não condicional e regressão de Poisson, respectivamente, utilizando-se o pacote estatístico Stata 7.0. Intervalos de confiança e efeitos do desenho foram considerados na avaliação da precisão das estimativas. Dois desfechos do estudo transversal com diferentes níveis de prevalência foram avaliados: vacinação contra influenza (66,1%) e doença pulmonar referida (6,9%). Na situação em que a prevalência foi alta, as estimativas das razões de prevalência foram mais conservadoras com intervalos de confiança menores. Na avaliação do desfecho de baixa prevalência, não se observaram grandes diferenças numéricas entre as estimações das razões de chances e razões de prevalência e erros-padrão obtidos por uma ou outra técnica. O efeito do desenho maior que a unidade indicou que a amostragem complexa, em ambos os casos, aumentou da variância das estimativas. Cabe ao pesquisador a escolha da técnica e do estimador mais adequado ao seu objeto de estudo, permanecendo a escolha no âmbito epidemiológico.

Factors associated with stages of change for red meat and vegetable intake by Japanese-Brazilians

Stages of change assess individual motivation for lifestyle changes, contributing to the development of more effective intervention strategies. The objective of the present study was to identify factors associated with stages of change for lower intake of red meat and higher intake of vegetables in a cross-sectional analysis of 578 Japanese-Brazilians aged 30-90 years. In adjusted logistic regression models, the odds ratios for women (OR = 1.89; 95%CI: 1.154; 3.103) and physically active individuals (OR = 1.00; 95%CI: 1.000; 1.001) were positively associated with stage of "action" for the higher intake of vegetables. Inverse associations were observed between central obesity (OR = 0.5; 95%CI: 0.351; 0.887) and highest tertile of red meat intake (OR = 0.50; 95%CI: 0.302; 0.817), as well as a positive association between age (OR = 1.04; 95%CI: 1.020; 1.070) and the stage of "action" to the lower intake of meat were verified. Motivation for Japanese-Brazilians to change their food intake was linked to lifestyle. Stage of change is an important factor in mediating food intake behavior change.

Fatores associados ao consumo de frutas e hortaliças no Brasil, 2006

OBJETIVO: Estimar a freqüência do consumo de frutas e hortaliças e fatores associados. MÉTODOS: Foram estudados 54.369 indivíduos com idade >18 anos, entrevistados pelo sistema de Vigilância de Fatores de Risco e Proteção para Doenças Crônicas por Inquérito Telefônico (VIGITEL) nas capitais brasileiras e Distrito Federal, em 2006. Os indicadores do consumo alimentar foram: consumo regular (>5 dias/semana) de frutas e hortaliças e consumo adequado (>5 vezes/dia). Calculou-se a prevalência dos indicadores e intervalos de confiança, estratificada por sexo. Para analisar a associação das variáveis sociodemográficas foram calculados odds ratio bruta e ajustada por sexo, idade, escolaridade e estado civil. RESULTADOS: Menos da metade dos indivíduos referiu consumo regular de fruta (44,1%) ou hortaliças (43,8%), enquanto 23,9% referiram consumo regular de frutas e hortaliças em conjunto; o consumo adequado foi referido por 7,3% dos entrevistados. O consumo de frutas e hortaliças variou entre as cidades estudadas, foi maior entre as mulheres e aumentou com a idade e escolaridade. CONCLUSÕES: Iniciativas de promoção do consumo de frutas e hortaliças devem atender a população como um todo, especialmente às cidades das regiões Norte e Nordeste, aos jovens, aos homens e aos estratos populacionais com baixa escolaridade.

Hipertensão em segmentos sociais pauperizados da região do Vale do Paraíba São Paulo

O objetivo deste trabalho foi verificar as relações entre fatores socioeconômicos, ambientais e biológicos com a hipertensão, segundo gênero. A população estudada foi formada por adultos residentes em dois municípios do Vale do Paraíba (SP), uma das regiões mais pobres do estado de São Paulo. Foi composta por 274 (39,8%) homens e 415 (60,2 %) mulheres. O estudo foi realizado por meio de um modelo de regressão logística hierarquizada, aplicado separadamente para homens e mulheres. Foram estimados os odds ratios ajustados (ORaj), com intervalo de confiança de 95% e a = 0,05. Para os homens, os seguintes fatores de risco estiveram associados à hipertensão: viver na zona rural (ORaj=2,00; p=0,01); etilismo (ORaj= 1,90; p=0,03) e idade acima de 40 anos (ORaj=3,10; p<0,0001). Famílias numerosas, com mais de seis pessoas exerceram efeito protetor (ORaj=0,46; p=0,02). Para mulheres, os fatores de risco associados foram: ausência de escolaridade (ORaj= 2,37; p=0,0003); sedentarismo (ORaj=1,71; p=0,04); obesidade acompanhada de baixa estatura (ORaj= 4,66; p <0,0001) e idade acima de 40 anos ( ORaj=5,29; p=0,01). A obesidade isolada não se associou à hipertensão, nos níveis pressóricos iguais ou maiores do que os correspondentes ao estágio II do padrão de referência.

Excesso de peso e hipertensão arterial em trabalhadores de empresas beneficiadas pelo Programa de Alimentação do Trabalhador (PAT)

OBJETIVO: Avaliar as prevalências de excesso de peso (EP), hipertensão arterial (HA) e fatores associados em trabalhadores de empresas beneficiadas pelo Programa de Alimentação do Trabalhador (PAT) da cidade de São Paulo. MÉTODOS: Estudo transversal com 1.339 trabalhadores de 30 empresas. A coleta de dados envolveu a aplicação de um questionário com dados de caracterização dos trabalhadores e peso e altura auto-referidos. Foi realizada a aferição da pressão arterial e o estado nutricional foi classificado segundo o Índice de Massa Corporal (IMC). Odds ratios foram estimadas na avaliação dos fatores de risco associados a HA e EP. RESULTADOS: Os trabalhadores apresentaram, em média, 36,4 anos (dp = 10,3) e 9,9 anos de estudo (dp = 2,3), sendo 60% da amostra pertencente ao sexo masculino. Na comparação com homens, mulheres apresentaram valores significativamente menores de idade, pressão arterial sistólica (PAS) e diastólica (PAD) e IMC e maior escolaridade. As prevalências em homens de EP (25 kg/m2) (56%) e de HA (PAS > 140 mmHg e/ou PAD > 90 mmHg ou uso de medicações anti-hipertensivas) (38%), foram aproximadamente o dobro da registrada em mulheres (30% e 19%), respectivamente. Idade foi fator de risco para a ocorrência de EP e HA em ambos os sexos, enquanto que a escolaridade foi fator de proteção para EP e HA em mulheres e fator de risco para o desenvolvimento de EP em homens. CONCLUSÃO: Os trabalhadores do sexo masculino constituíram uma população de maior risco para ocorrência de HA e EP e devem ser priorizados nos programas que visam a prevenção dessas doenças. Neste sentido, o PAT pode representar um lugar de destaque nas ações de saúde e nutrição no ambiente de trabalho.

Situação epidemiológica da brucelose bovina no Estado do Mato Grosso do Sul

Realizou-se um estudo para caracterizar a situação epidemiológica da brucelose bovina no Estado de Mato Grosso do Sul. Foram definidos três estratos (regiões): Pantanal-corte, Planalto-corte e Planalto-leite, este último subdividido em Bolsão, Campo Grande e Dourados. Em cada estrato foram amostradas aleatoriamente propriedades e, dentro dessas, foi escolhido, de forma aleatória, um número pré-estabelecido de animais, dos quais foi obtida uma amostra de sangue. No total, foram amostrados 14.849 animais, provenientes de 1.004 propriedades. Em cada propriedade amostrada foi aplicado um questionário epidemiológico para verificar suas características e também para detectar transtornos reprodutivos que poderiam estar associados à infecção brucélica. O teste utilizado foi o do antígeno acidificado tamponado. O rebanho foi considerado positivo se pelo menos um animal foi reagente à prova sorológica. Para o Estado, a prevalência de focos foi de 41,5% [36,5-44,7%]. As prevalências de focos e de animais infectados por estrato foram, respectivamente, de: 59,0% [52,8-64,9%] e 12,6% [9,1-17,2%] para o estrato Pantanal-corte, e 40,6% [35,8-45,5%] e 4,5% [2,1-9,0%] para Planalto-corte. No estrato Planalto-leite, a prevalência de focos foi de 33,1% [28,4-38,1%]. Os fatores de risco (odds ratios, OR) associados à condição de foco foram: ter ≥500 vacas (OR = 2,46 [1,81-3,34]), ocorrência de bezerros fracos (OR = 1,20 [0,87-1,65]) e uso da inseminação artificial (OR = 0,71 [0,50-1,01]).