Objectives Previous studies found that low education or income level was associated with insufficient fruit and vegetable consumption (IFVC) among the general population. However, cancer survivors can be heterogeneous from the general population in many aspects. Our objective was to disentangle their association among cancer survivors.
Design Nationwide cross-sectional survey in the USA.
Setting 2017 Behaviour Risk Factor Surveillance System.
Participants 5409 cancer survivors.
Exposure and outcome Educational level (graduated from college/technical school, attended college/technical school and high school or less) and annual household income (≥US$75 000, US$35 000 to <US$75 000 and <US$35 000) were exposures of interest. IFVC, which was defined as <5 servings/day according to the American Cancer Society recommendation, was treated as the outcome.
Data analysis Multivariable logistic regression corrected for sampling weight was performed to estimate the association. Subgroup analyses and interaction tests were performed by age, gender, obesity and physical activity.
Results Overall, 4750 survivors (weighted percentage: 88.5%) had IFVC. Participants with lower education had a significantly higher rate of IFVC (high school or less vs college graduates: adjusted OR=2.17, 95% CI 1.45 to 3.25, p trend <0.01). The association between income and IFVC was almost null. Associations did not differ in most subgroups; however, the association of lower education appeared to be more substantial among physically inactive survivors (p interaction <0.01).
Conclusion Low educational background, not low income, was associated with IFVC among cancer survivors. Prospective cohort studies are needed to verify the conclusion.
- medical education & training
- nutrition & dietetics
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Strengths and limitations of this study
The large sample size in Behavioural Risk Factor Surveillance System (BRFSS) ensures a good power and reduces imprecision.
Subgroup analysis helps us verify whether the impact of education is stronger in certain groups, like physically inactive survivors.
Cancer diagnosis was measured by self-report, which is less valid compared with medical record review.
BRFSS measured fruit and vegetable consumption during the past 1 month, which might not be sufficient to reflect participants’ long-term or constant intake level.
Several decades ago, cancer was a refractory disease due to the lack of accurate detection methods and effective antitumour medication. However, improvements in medical techniques and clinical treatment modalities have allowed a great proportion of patients with cancer to survive for longer periods of time after diagnosis.1 To date, the number of cancer survivors continues to increase and now accounts for about 5% of the US population.2 More than 16.9 million people in the USA have personal histories of cancer in 2019 and this number is estimated to reach 22.1 million by 2030.1 This trajectory underscores the importance of tertiary prevention in cancer survivors, which can help survivors maintain general health and promote quality of life.
A diet with sufficient fruit and vegetable can be beneficial to cancer survivors, which is critical in tertiary prevention.3 Fruit and vegetable contain a myriad of nutrients and phytochemicals, including fibre, vitamins, antioxidants, potassium, flavonoids and other compounds4 that potentially inhibit cancer progression5 and reduce mortality.6 7 Epidemiological studies have shown that a diet with sufficient fruit and vegetable was associated with a lower mortality in breast6 and colon cancer survivors7 as well as better quality of life.8 The American Cancer Society (ACS) suggests that cancer survivors should consume at least five servings of fruit and vegetable per day.9 However, previous research shows that only a small fraction (15%–20%) of survivors have sufficient fruit and vegetable intake.10
Previous studies found that unfavourable education or income level was associated with insufficient fruit and vegetable consumption (IFVC) among the general population.11 A systematic review focusing on low-income and middle-income countries found that high socioeconomic status (measured through education, income or composite indicators) was associated with higher fruit and/or vegetable consumption, diet quality and food diversity.12 However, cancer survivors can be heterogeneous from the general population in many aspects. For example, due to high medical expenditure, many survivors experience economic hardship,13 which may affect their fruit and vegetable purchase. Survivors with higher education are more likely to change their dietary habits14 when being informed of cancer diagnosis. Such evidence suggests that the association pattern of education or income among cancer survivors may differ from that of the general population. Given the limited evidence regarding associations between educational background and income and fruit and vegetable consumption among cancer survivors, we used the 2017 Behavioural Risk Factor Surveillance System (BRFSS) data to disentangle these relationships.
BRFSS and study population
BRFSS is an annual cross-sectional telephone survey conducted in the USA since 1984 by the Centres for Disease Control and Prevention. The survey collects data from adult US residents (≥18 years) regarding their health-related risk behaviours, chronic health conditions and use of preventive services. Survey questions went through technical review, cognitive testing and field testing before being placed on the questionnaire. The BRFSS collects information from all 50 states, the District of Columbia, Puerto Rico, the US Virgin Islands, Guam, American Samoa and Palau. Detailed information about BRFSS can be found at www.cdc.gov/brfss/about/index.htm. For our current study, a total of 5409 cancer survivors without missing data of exposure, outcome and other covariates were included for analysis. Specifically, we treated cancer survivors as people self-reporting histories of cancer diagnosis based on definitions from the National Coalition for Cancer Survivorship.15
Patient and public involvement
Survey respondents were selected as described above and were not involved in the design of this study.
The 2017 BRFSS asked four questions to assess how many servings of fruit and vegetable participants consumed per day during the past month, which included intake of the following items: (1) fruit (non-juice), (2) dark green vegetable, (3) potato (not including fries or fried potato) and (4) other types of vegetable. We defined IFVC as <5 servings/day.16 17
Educational background and annual household income were exposures of interest in the analysis. Participants self-reported the highest grade or year of school completed as well as the annual household income from all sources in the BRFSS. We categorised education and income as the following ordinal variables to ensure each level had sufficient and similar number of observations: (1) education: graduated from college/technical school, attended college/technical school and high school or less and (2) income: ≥US$75 000, US$35 000 to <US$75 000 and <US$35 000.
Demographic characteristics included age, gender, race and marital status. We treated age as an ordinal variable (<65, 65–74 and ≥75 years) to approximate tertiles. We categorised race as white, black and other. We reclassified self-reported marital status as married (married couple or member of an unmarried couple) and not married (never married, divorced, widowed or separated) because being unmarried could be associated with a significant decrease in quantity and variety of fruit and vegetable intake.18 Health-related lifestyle indicators, which included smoking, alcohol drinking, obesity and physical activity, were included for analysis since they were closely associated with our exposures of interest and dietary behaviours.19 We categorised smoking status as never smoked, current smoker or former smoker. We defined heavy alcohol drinking as consuming ≥14 drinks/week for male respondents or ≥7 drinks/week for female respondents.20 Obesity was defined as having a body mass index ≥30 kg/m2. Physical inactivity was defined as having no physical activity or exercise (eg, running, callisthenics, golf, gardening or walking) during the past month.21 The BRFSS treated respondents’ general health as a binary variable (fair or poor vs good, very good or excellent).22 Major comorbidities, including diabetes mellitus, high blood cholesterol, high blood pressure, myocardial infarction, coronary heart disease, stroke, chronic kidney disease, arthritis, asthma, chronic obstructive pulmonary disease and depressive disorder, were also measured via self-report. Participants’ self-reported histories of routine clinical check-ups and healthcare coverage that included health insurance, prepaid plans (eg, Health Maintenance Organization), government plans (eg, Medicare) and Indian Health Service.23 Cancer-related indicators included time elapsed since cancer diagnosis, number of cancers diagnosed and cancer type.
All sociodemographic and health-related factors were selected based on previously published articles and a priori knowledge regarding the associations between these factors and our exposures of interest and IFVC.
As this is a complete-case analysis, no statistical method was used to handle missing data. The 2017 BRFSS used iterative proportional fitting to weight data. This allowed incorporation of telephone survey data and introduction of more demographic characteristics, which better reflected the sociodemographic distribution of each individual state. We used number of observations and weighted percentages (%) of covariates to descriptively summarise the overall sample and subpopulation defined by IFVC, and we used χ2 tests to compare distributions of these covariates by IFVC. When summarising education and income, we reported number of observations for each level and calculated weighted point estimates and 95%CIs of IFVC prevalence. We used logistic regression corrected for sampling weight to estimate ORs and 95% CIs of education and income. In crude models, only one independent variable (education or income) was included. In multivariable logistic regression, we included education and income simultaneously and adjusted for age, gender, race, marital status, smoking status, alcohol drinking, physical activity, obesity, general health, number of comorbidities, healthcare coverage, clinical check-up, comorbidity, time elapsed since cancer diagnosis and number of cancers. We conducted tests for trends by treating education and income as continuous variables in the model. Based on parameters in the multivariable model, we used ‘margins’ in Stata with unconditional variance–covariance matrix to calculate model-adjusted probability of IFVC by education levels within each stratum of income (or by income levels within each education stratum). Two sets of sensitivity analyses were conducted in addition to the primary logistic regression models. Specifically, the sensitivity analysis was restricted to survivors who only had one cancer (n=4284) or survived for more than 1 year (n=4699) to preclude the impact from antitumour treatment that might affect dietary behaviours. To verify the robustness of primary analysis, we used a linear regression model treating fruit and vegetable consumption as a continuous variable to calculate the mean difference for education and income; the model adjusted for the same set of covariates.
Several factors, including age (<65 vs ≥65 years), gender (female vs male) and health-related factors, could substantially affect people’s dietary pattern.24–27 Thus, we conducted subgroup analyses stratified by these variables to explore if there were interactions between education and income and these factors in relation to IFVC. We chose obesity and physical inactivity as the indicators of adverse lifestyle factors; smoking and heavy alcohol drinking were not considered due to the uneven distribution within the variable. We added interaction terms between education and income and age, gender, obesity and physical inactivity into the model and used Wald tests to examine whether there was a significant interaction. In addition, we estimated adjusted OR (aOR) and model-adjusted probability of IFVC for breast and prostate cancer and melanoma because they had large sample sizes compared with other types of cancer and their favourable survival endowed more opportunities for tertiary prevention.
For current analysis, two-sided p values <0.05 were considered to be statistically significant. All statistical analyses were conducted using Stata, V.15.0 (College Station, Texas, USA: StataCorp, LLP).
Table 1 descriptively summarises demographic characteristics and health-related factors of the overall sample. Among the 5409 cancer survivors, 4750 (weighted percentage: 88.5%) had IFVC. Overall, most of the participants were aged ≥65 (64.5%) years and the mean age was 66.9 (SD: 11.0) years. Over half of the survivors were women (57.2%) and the majority of survivors was white (94.1%). Over one-third of study participants were unmarried (39.4%). In terms of lifestyle behaviours, approximately half of the survivors were never-smokers (52.0%), most survivors were not heavy drinkers (95.4%) and 28.1% of survivors were physically inactive during the past month. Prevalence of obesity was 34.7% and about a quarter (25.7%) of survivors were living with poor or fair general health. By pooling all types of comorbidities, the data showed only 11.3% had no comorbidity, while 18.6% had one comorbidity and 70.1% had at least two comorbidities. Most survivors (84.6%) reported that they had a clinical check-up last year and 97.4% had healthcare coverage. Overall, about half (51.5%) of the survivors had cancer diagnoses within the recent 10 years and 79.2% of them had only one cancer. In aspects of cancer type, the prevalence of female breast cancer, prostate cancer, gastrointestinal cancer and melanoma was 15.5%, 10.1%, 5.1% and 13.2%, respectively. Pearson’s χ2 tests indicated that survivors who were men, not married, current smoker, physically inactive, obese, self-reporting a favourable general health or living with ≥2 comorbidities were more likely to have IFVC (ps<0.05).
Educational level and household income were evenly distributed and two-sample proportion tests showed that the weighted prevalence of IFVC increased with the decline of educational level and household income. Overall, participants with an education background at or lower than high school, as compared with those graduating from college or technical school, had a significantly higher rate of IFVC (crude OR (cOR)=2.76, 95% CI 1.91 to 3.98; aOR=2.17, 95% CI 1.45 to 3.25) in both crude and multivariable models; the statistical test suggested a significant trend (p trend <0.01). Although the crude model showed a significant association between household income and IFVC (<US$35 000 vs ≥US$75 000/year: cOR=2.00, 95% CI 1.38 to 2.89, p trend <0.01), the effect measure turned null in the multivariable analysis (<US$35 000 vs ≥US$75 000/year: aOR=1.02, 95% CI 0.65 to 1.62, p trend=0.90) (table 2). Effect measures of other covariates are presented in online supplemental table 1. Association patterns of education and income among survivors with only one cancer and survivors living for more than 1 year after cancer diagnosis were largely similar to estimates obtained in the primary analysis (table 2). By treating fruit and vegetable servings as the outcome in multivariable linear regression, the model suggested that lower educational level was significantly associated with an increased fruit and vegetable consumption; effect measures of income were non-significant in linear regression (see online supplemental table 2).
Results of model-adjusted probability (figure 1A, B) showed the same association patterns as the primary analysis. Specifically, probability of IFVC was very similar across different levels of income regardless of educational attainment; in each stratum of income, the probability of IFVC increased as educational level decreased. Detailed estimates are included in online supplemental table 3.
The association of IFVC with education and income did not differ in subgroups defined by age, gender and obesity (table 3). The aORs of educational levels among each age group were similar to those in primary multivariable analysis (p interaction=0.83, p trend <0.01 for age <65 years, p trend=0.01 for age ≥65 years). Although point estimates of aORs of lower income (<US$35 000) were in different directions by age groups, the Wald test did not support a significant interaction either (p interaction=0.08). There was no evidence suggesting a significant interaction between education/income and gender in relation to IFVC (p interaction=0.20 for education, p interaction=0.75 for income). There was no significant interaction between obesity and education/income in relation to IFVC (p interaction=0.42 for education, p interaction=0.20 for income). However, results (table 3) showed that the impact of lower educational level was more substantial among survivors with inactive lifestyle (high school or less vs graduated from college/technical school: aOR=6.21, 95% CI 2.98 to 12.93, p interaction <0.01); no significant interaction was observed between inactivity and income (p interaction=0.07).
A positive association between low education (high school or less vs graduated from college) and IFVC was observed for breast cancer (aOR=2.73, 95% CI 1.52 to 4.88, p trend <0.01) and melanoma (aOR=1.92, 95% CI 0.98 to 3.77, p trend=0.04), although statistical significance was not observed for the latter; effect measures of education among prostate cancer survivors were not significant. There were no significant associations between income and IFVC for breast and prostate cancer and melanoma (see online supplemental table 4). Model-adjusted probability of IFVC among survivors of breast and prostate cancer and melanoma is presented in online supplemental table 5.
In general, we found that a high rate (88.5%) of participants did not adhere to the ACS recommended five servings of fruit and vegetable per day. Low-level education was found to be positively associated with IFVC. While low-level household income was also positively associated with IFVC in unadjusted logistic regression, the relationship was not significant in the multivariable logistic regression. The association patterns were largely unchanged among cancer survivors with only one cancer or surviving for more than 1 year since diagnosis. The impact of lower education on IFVC appeared to be more substantial among physically inactive survivors, whereas there was no significant interaction between age, gender or obesity and education in relation to IFVC. No interaction was observed for income.
The findings on educational level are in line with conclusions from previous population-based research, but the results on income are not consistent. Mayer et al investigated 619 cancer survivors using a nationwide survey in the USA during 2002–2003 and reported that survivors with an education background lower than high school were less likely to eat at least five servings of fruit or vegetable per day (OR=0.6, 95% CI 0.4 to 0.8).28 Given the potential secular variation, cancer survivors of the current era may have different dietary patterns or health awareness compared with survivors studied 15 years ago, suggesting the conclusions need further verification using a more recent data. Another population-based study in the USA analysed 2865 breast cancer survivors and found that, when compared with their peers with education at or less than high school, women who had graduated from college were more likely to have a substantial increase in fruit and vegetable consumption after cancer diagnosis, although the association patterns of income were largely non-significant.29 However, it did not disentangle whether survivors with favourable educational background or income level were more likely to meet the recommended dietary requirement. A prospective study measured average fruit and vegetable intake of 2134 prostate cancer survivors during 2004–2005 and reported positive associations of consumption level with education and income; however, this outcome was based on a χ2 test and could be biassed due to confounders.30 These issues were carefully considered and addressed in current analysis by using the recent nationwide survey data.
We have some speculations about mechanisms behind the association patterns in our analysis. First, several studies show that education can improve survivors’ health awareness. Advanced education can help survivors better understand health benefits of eating sufficient fruit and vegetable like progression risk reduction and improvement in survival30 31; this may finally reduce their likelihood of low-level intake.32 33 Second, education decreases worry and fear of cancer harm (eg, shorter life expectancy, recurrence and lower life quality),34 which can be barriers to healthy dietary behaviours.35 For example, Skaali et al34 showed that medium-level education (11–12 years), as compared with high-level education (≥13 years), was significantly associated with a higher fear of recurrence score among 1336 long-term testicular cancer survivors (OR=1.51, 95% CI 1.18 to 1.93) in Norway. Third, we speculate that educational level can be the key confounder between income and IFVC because the effect measures of income became null when education and income were included in the multivariable model simultaneously and the a priori knowledge suggested income could be a surrogate or downstream event of educational attainment.36 This may imply that individuals’ food intakes are influenced more by their educational attainment than the adequacy of their household incomes. Finally, physical inactivity is an indicator of adverse lifestyle behaviour and it may have synergistic effects with poor health awareness conferred by low education,37 38 which partially explains why the effect measures of low-level education are more substantial among inactive survivors.
The current study has several strengths in design and analysis. To our knowledge, this is the first study to use BRFSS data to characterise associations between education and income and IFVC among cancer survivors; the large sample size in BRFSS ensures a good power for statistical analysis and reduces imprecision. Second, the weighted analysis reduces impact of selection bias and multiple sets of sensitivity analyses further validate robustness of the association identified in the primary analysis. Additionally, potential effect modification by several covariates has been investigated in subgroup analyses and can help us verify if the impact of education or income is stronger in certain groups, allowing researchers to establish a more targeted health intervention programme. However, several limitations should be considered when interpreting the results. First, cancer diagnosis and other illnesses were all measured by self-report, which can be less valid compared with medical record review. Second, the BRFSS lacks discrimination among the categories of fruit and vegetable intake, and it only measured fruit and vegetable consumption during the past 1 month, which might not be sufficient to reflect participants’ long-term or constant intake level. Besides, we could not ascertain whether the current dietary behaviour represents an improvement when compared with dietary behaviour before cancer diagnosis. The high prevalence of IFVC among cancer survivors may mask the insufficient attempt to enhance the dietary behaviour. Third, survivors of gastrointestinal cancer are more likely to be affected in aspects of dietary behaviours due to clinical characteristics and treatments of the tumour,39 whereas numbers of survivors of oesophageal, gastric and colorectal cancer are very limited in the BRFSS data set, making the conclusion less generalisable to these survivors. Finally, the 2017 BRFSS is a cross-sectional study and causal relationship between exposures and outcome cannot be investigated.
Our study provides several health implications. Particularly, the results suggest that education plays a key role in survivors’ adherence to the ACS recommendation of five servings of fruit and vegetable each day and increasing survivors’ health awareness and knowledge can be fundamental in dietary intervention. While educational attainment can hardly be modifiable, diet-related health education is viable as shown in several knowledge-based dietary intervention programmes,40 especially for cancer survivors with low education background. In conclusion, this research suggests that low education background, but not low income, maybe a barrier to fruit and vegetable consumption among cancer survivors. Such effects may differ by negative lifestyle factors like physical inactivity, but this needs further verification in studies with more comprehensive measures of lifestyle behaviours. Future studies with a comprehensive measure of dietary intake (eg, the category and amount) will be needed to verify the conclusions in this study.
We thank Anthony Chicaiza of the Georgetown University Lombardi Comprehensive Cancer Center for language editing and proofreading. The authors appreciate research staff participating in BRFSS data collection, management and dissemination.
Contributors All of the authors contributed to this work. ZZ and DZ designed the study. ZZ and DZ conducted statistical analysis. ZZ and DZ drafted the manuscript. ZZ, DZ, JH-yW, YQ, YL and DB participated in discussion and manuscript revision. All authors have approved the final version of the manuscript.
Funding This work was supported by Doctoral Student Innovation Fund, Peking Union Medical College PN: 2018-10001-06.
Competing interests None declared.
Patient consent for publication Not required.
Ethics approval We used publicly available deidentified data, which do not require IRB approval.
Provenance and peer review Not commissioned; externally peer reviewed.
Data availability statement Data are available in a public, open access repository.
Supplemental material This content has been supplied by the author(s). It has not been vetted by BMJ Publishing Group Limited (BMJ) and may not have been peer-reviewed. Any opinions or recommendations discussed are solely those of the author(s) and are not endorsed by BMJ. BMJ disclaims all liability and responsibility arising from any reliance placed on the content. Where the content includes any translated material, BMJ does not warrant the accuracy and reliability of the translations (including but not limited to local regulations, clinical guidelines, terminology, drug names and drug dosages), and is not responsible for any error and/or omissions arising from translation and adaptation or otherwise.
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