Intended for healthcare professionals


Ecological analysis of ethnic differences in relation between tuberculosis and poverty

BMJ 1999; 319 doi: (Published 16 October 1999) Cite this as: BMJ 1999;319:1031
  1. Jeremy I Hawker, consultant epidemiologist (jhawker{at},
  2. Surinder S Bakhshi, consultant in communicable disease controlb,
  3. Shaukat Ali, research associateb,
  4. C Paddy Farrington, senior statisticianc
  1. a Public Health Laboratory Service Communicable Disease Surveillance Centre (West Midlands), Birmingham Heartlands Hospital, Bordesley Green East, Birmingham B9 5SS
  2. b Birmingham Health Authority, St Chads Court, Birmingham B16 9RG
  3. c Department of Statistics, Open University, Walton Hall, Milton Keynes MK7 6AA
  1. Correspondence to: J I Hawker
  • Accepted 9 June 1999


Objective: To examine the effect of ethnicity on the relation between tuberculosis and deprivation.

Design: Retrospective ecological study comparing incidence of tuberculosis in white and south Asian residents of the 39 electoral wards in Birmingham with ethnic specific indices of deprivation.

Setting: Birmingham, 1989-93.

Subjects: 1516 notified cases of tuberculosis.

Main outcome measures: Rates of tuberculosis and measures of deprivation.

Results: Univariate analysis showed significant associations of tuberculosis rates for the whole population with several indices of deprivation (P<0.01) and with the proportion of the population of south Asian origin (P<0.01). All deprivation covariates were positively associated with each other but on multiple regression, higher level of overcrowding was independently associated with tuberculosis rates. For the white population, overcrowding was associated with tuberculosis rates independently of other variables (P=0.0036). No relation with deprivation was found for the south Asian population in either single or multivariable analyses.

Conclusions: Poverty is significantly associated with tuberculosis in the white population, but no such relation exists for those of Asian ethnicity. These findings suggest that causal factors, and therefore potential interventions, will also differ by ethnic group.

Key messages

  • Previous studies in the United Kingdom have been unable to disentangle the effects of poverty and ethnicity on the incidence of tuberculosis

  • A strong relation was found between measures of poverty and tuberculosis in the white population

  • No relation between measures of poverty and tuberculosis was found in the Asian population

  • The only measure of poverty independently associated with tuberculosis in the white population is overcrowding

  • An increasing proportion of tuberculosis is occurring in Asian people and causal factors in this group are likely to be different from those in the white population


Tuberculosis has been linked with poverty since the 19th century.1 Notification rates for tuberculosis have fallen substantially in England and Wales this century,2 coinciding with improving living conditions and improved treatment However, since the 1960s this decline has slowed, with an increasing proportion of cases occurring in immigrants from countries with a high prevalence of tuberculosis.2 The proportion of notified cases in the United Kingdom among people of south Asian origin (hereafter termed Asians) has increased successively in the six national surveys carried out between 1965 and 1993 to 41% of cases, whereas the proportion in white people has fallen to 44%.3

Recent ecological studies in Liverpool and elderly people in Leeds suggest that tuberculosis is associated with various indices of deprivation 4 5 However, neither of these studies was able to analyse this relation by ethnic group. Disentangling the effects of deprivation from those of belonging to an ethnic minority on the incidence of tuberculosis is difficult,6 but to attempt to do so is important. The epidemiology of tuberculosis differs considerably with ethnicity. Asian people predominantly acquire new infection from infected people in the same community or when visiting the Indian subcontinent,7 but white people generally have reactivation of endogenous latent infection.8 This distinction is reflected in the differences in the age distribution of cases and in the type of disease between ethnic groups. In the 1988 national survey, 55% of white people with tuberculosis were over 55 years old compared with only 16% of Asians, and 16% of white patients had only non-respiratory tuberculosis compared with 36% of Asian patients.9 Indeed, age is an important risk factor affecting the magnitude of tuberculosis morbidity in the population,10 but the age distribution of the population of these two ethnic groups differs considerably. It is therefore not safe to assume that social factors which affect tuberculosis incidence in one of these ethnic groups will do so for the other. We attempted to discover whether the link between tuberculosis and deprivation holds true in Birmingham for the whole population and for white and Asian ethnic groups analysed separately.


We obtained details of notifications of tuberculosis (excluding chemoprophylaxis) in Birmingham for the five years 1989-93 from the Birmingham tuberculosis notification register. Patients are asked to indicate their ethnic group (Asian, white, black Caribbean, or other), which is recorded on the tuberculosis register by staff at the Birmingham chest clinic. The electoral ward of residence is obtained from the recorded home address.

We used 1991 census data to provide denominators to calculate specific mean annual notification rates per 100 000 population for each ethnic group in each of the 39 electoral wards in Birmingham. We added 0.5 to each ward count of tuberculosis cases to reduce biases associated with zero counts. The census data were also used to obtain the following indices of deprivation: proportion of households with more than 1.5 people per room; proportion of households with more than one person per room; proportion of residents in households with more than 1.5 people per room; proportion of households not owner occupied; proportion of residents in households lacking central heating; proportion of households with no car; proportion of residents in households with no car; proportion of residents unemployed. These covariates were calculated separately for white and Asian residents and households in which the head of the household was white or Asian. Other covariates used were the Townsend score, which is derived from four of these variables,11 and, for the analysis of total population tuberculosis, the proportion of the population of Asian ethnicity.

We used Box-Cox profiles12 to assess the need for transformations of the rates. In all cases the square root transformation was found adequate. Wards were weighted according to ward populations. For regressions involving only Asians or white people, the Asian or white ward populations, respectively, were used We used S-plus software for multiple weighted linear regression of the square roots of the tuberculosis rates against predictor variables and diagnostic checks (using residual plots) of the validity of the model.13


During the study period, 1516 cases of tuberculosis were notified in Birmingham, of which 995 (66%) were in Asians and 332 (22%) in white people. The crude annual notification rates were 153/100 000 population for Asian people and 8.8/100 000 for white people, a 17-fold difference. Table 1 gives the age distribution of cases in the two ethnic groups.

Table 1.

Tuberculosis cases by ethnic group and age group

View this table:

Total population analysis

In single variable analyses all but two of the 10 covariates were strongly positively associated with tuberculosis (P<0.01 in each case). The exceptions were the proportion of households not owning their own homes (P=0.09) and the proportion of residents without central heating (P=0.069) However, all these covariates were positively correlated. In multiple regression the only variables independently associated with tuberculosis were the two overcrowding variables. These two variables were themselves dependent. Table 2 shows three models for overcrowding (models (a)-(c)). Model (c) shows that when both overcrowding variables are fitted together, one has a negative coefficient that partly compensates for the other. Overall the models indicate a positive relation with high levels of overcrowding (fig 1). The proportion of Asian residents was not independently associated with tuberculosis (table 2 (d)).

Table 2.

Parameter estimates (SE) of overcrowding and proportion of Asian residents for whole population with four regression models

View this table:
Fig 1.
Fig 1.

Relation between tuberculosis rate and overcrowding for whole population. Each point represents one electoral ward

However, the differences in both tuberculosis rates and deprivation indices between the Asian and white community, shown in table 3 and figure 2, throw doubt on the validity of such grouped analyses. Specifically, the relation between deprivation and tuberculosis at the individual level may be confounded by ethnicity. Figure 3 shows that the level of overcrowding is strongly correlated with the proportion of the population of Asian ethnicity.

Table 3.

Median values for tuberculosis rate and selected covariates in 39 electoral wards by ethnic group and overall population

View this table:
Fig 2.
Fig 2.

Relation between tuberculosis rate and overcrowding by ethnic group. Figures are annual averages and each point represents one electoral ward

Fig 3.
Fig 3.

Relation between overcrowding and percentage of resident population of Asian ethnicity. Each point represents one electoral ward

Analysis by ethnic group

Figure 2 shows the tuberculosis rates plotted against the proportions of households with more than 1.5 people per room for the white and Asian populations. In single variable analyses for white residents the only variables significantly associated with tuberculosis rates were the proportion of households with more than 1.5 people per room (P=0.0036) and the proportions of residents in such households (P=0.0085), both of which were positively associated with tuberculosis rates. In multiple regression analysis the only variable independently associated with tuberculosis was the proportion of households with more than 1.5 people per room. The regression parameter estimate was 2.63 (SE 0.85).

For the Asian population, no single variable was significantly associated with tuberculosis—for example, the proportion of households with more than 1.5 people per room had a regression coefficient of 0.433 (SE 0.313, P=0.18). The only covariate approaching significance was the proportion of households not owning their own home, which was marginally positively associated (regression parameter estimate 0.186, SE 0.098, P=0.067).


We found significant associations between markers of deprivation and incidence of tuberculosis for the white population but not for the Asian population. This implies that the association between poverty and tuberculosis previously demonstrated 4 5 may not be generalisable to non-white ethnic groups, which now account for more than half of cases of tuberculosis in the United Kingdom.3

Our study suggests two possible explanations for the association with poverty found by the earlier studies which did not separate ethnic groups on both predictor (deprivation) and outcome (tuberculosis) variables The first is that the relation found at the whole population level (confirmed by our study) may simply reflect the relation between poverty and tuberculosis in the white population. Both the Liverpool4 and Leeds5 studies were carried out in populations that are likely to be predominantly white: Liverpool has a relatively small ethnic minority population, especially of south Asians,4 and ethnic minorities are likely to be under-represented in the elderly people studied in Leeds. This explanation is consistent with the finding that increasing deprivation has a greater effect on tuberculosis rates in areas with small immigrant populations than in areas with more immigrants.14

The second possible explanation is that markers of deprivation and the proportion of the population of Asian origin are confounded at the ecological level because ethnic minorities tend to live in poorer areas. These variables therefore are impossible to disentangle without using data on ethnic group. This situation is certainly true for Birmingham (fig 3) and London.15 The explanation is consistent with findings in two ecological studies which looked at trends in tuberculosis: a study of all districts in England and Wales found that whereas 29% of cases occurred in 10% of districts with the highest Jarman score, 33% occurred in the districts with the highest proportion of ethnic minority residents,16 and a study of London boroughs found significant associations with both proportion of migrants and overcrowding but no independent association with unemployment and social class.17

Potential biases and confounders

Caution is needed when drawing conclusions about causation from ecological studies as they may not properly reflect association at the individual level because of confounding or modification of effect.18 In addition, regression analyses depend on the estimates of tuberculosis rates in each ward, and although this study contains four times as many cases as that in Liverpool and 15 times as many as that in Leeds, some of the ethnic specific ward rates are based on small numbers of cases. The precision of the rates is likely to depend on population size. We addressed this problem by weighting individual observations by population size, although an unweighted analysis produced similar results.

The lack of any association between poverty and tuberculosis in Asian people in our study is unlikely to be due to sample size (there were three times as many Asian patients as white ones) or insufficient variation between Asian populations in different wards. Although it is possible that the indices of deprivation used are not applicable between ethnic groups, it is unlikely that none of the 10 indices we used are valid proxies for deprivation in the Asian population. It therefore seems likely that other factors explain the variations in tuberculosis rates in this group. We suggest that the likelihood of close contact with an infectious case of tuberculosis is the key factor. This is supported by the observation that 20% of tuberculosis cases occurred within 12 months after a visit to the Indian subcontinent.7 Indeed, the ability to afford such a visit may have a confounding effect on the relation between poverty and tuberculosis.

The finding on multivariable analysis that overcrowding was the only factor associated with tuberculosis rates in white people independently of other variables was unexpected. If tuberculosis in white people is usually reactivation of latent infection then the mechanism of a cause and effect relation with overcrowding is not obvious. It may be that interactions between variables make multiple regression at the ecological level unreliable or that overcrowding is a marker for another factor that we could not measure, such as diet or education.


Our results support the conclusion that social factors, such as poverty, which influence the likelihood of developing (predominantly reactivated) tuberculosis in white people are likely to be different from those influencing the risk of contracting (predominantly new infection) tuberculosis in the Asian population.19 Further research is necessary, including a case-control study to disentangle the confounding effects of poverty, ethnicity, and age at the individual level. In addition, recent developments in DNA analysis of Mycobacterium tuberculosis20 could be used to study patterns of transmission within and between ethnic groups. In the meantime, as national notification rates are 25 times higher in Asians than white people (and this inequality is widening),3 prevention of new infection in Asians by education,21 immunisation,22 and prompt diagnosis and treatment of infectious cases23 must remain a priority.


We thank Dr John Innes and the staff at Birmingham chest clinic for their work in maintaining the Birmingham tuberculosis register.

Contributors: JIH contributed to the formulation of the primary study hypothesis and led the design of the study, interpretation of the results, and writing of the paper. SSB contributed to formulation of the hypothesis, interpretation of the data, and writing the paper. SA collected all the data and contributed to the analysis of the data and writing of the paper. CPF led the analysis of the data and contributed to the design of the study, interpretation of results, and writing the paper. JIH will act as guarantor.


  • Funding None.

  • Competing interests None declared.


  1. 1.
  2. 2.
  3. 3.
  4. 4.
  5. 5.
  6. 6.
  7. 7.
  8. 8.
  9. 9.
  10. 10.
  11. 11.
  12. 12.
  13. 13.
  14. 14.
  15. 15.
  16. 16.
  17. 17.
  18. 18.
  19. 19.
  20. 20.
  21. 21.
  22. 22.
  23. 23.
View Abstract