Cohen’s κ statistic for all duplicate-screened sections was 0.78, reflecting excellent agreement between reviewers [57].
Characteristics of included studies
Our search yielded 5200 unique records, of which 37 met the inclusion criteria (ESM Fig. 1). Individual study characteristics are presented in Table 1 and aggregate study characteristics in Table 2 (additional detail in ESM Table 2). Nine studies examined breast cancer screening [65, 71,72,73,74,75,76,77,78], two examined cervical cancer screening [79, 80], and eight examined colorectal cancer screening alone [59, 65, 66, 70, 81,82,83,84,85]; eight studies examined both breast and cervical cancer screening [86,87,88,89,90,91,92,93], one examined breast and colorectal cancer screening [94], and nine examined all three cancer screenings [95,96,97,98,99,100,101,102,103]. All studies were observational, with 25 cross-sectional [65, 70, 77,78,79,80, 82,83,84,85, 87,88,89,90,91,92,93, 95,96,97,98,99,100, 102, 103] and 12 cohort [59, 65, 71,72,73,74,75,76, 81, 86, 94, 101] designs, including one RCT assessing the effect of diabetes on colorectal cancer screening completion independent of the intervention [59]. Over half of the studies were conducted in North America, with 21 studies from the USA [59, 66, 70,71,72, 78, 81,82,83, 85, 86, 89, 90, 94,95,96,97,98, 101,102,103] and three from Canada [73, 75, 84]. The remaining studies were from Europe [65, 76, 80, 88, 91,92,93, 99, 100], the Middle East [74, 77] and Asia [79, 87]. Sample sizes ranged from 129 to 732,687 individuals and the mean sample diabetes prevalence was 15.1% for breast, 9.7% for cervical and 12.4% for colorectal cancer screening.
Table 1 Characteristics of the included studies Table 2 Aggregate characteristics of the included studies by cancer screening site
Assessment of methodological quality
Methodological quality varied across studies (ESM Table 3). Overall, only nine studies [59, 65, 71,72,73,74,75, 81, 94] were rated as high quality (>6 points) and all were cohort designs. Nearly all studies were conducted in large population-based samples. Over half of the cross-sectional studies did not justify their sample sizes [70, 77, 78, 83, 85, 87,88,89,90, 96,97,98, 100, 103], which poses a risk of underpowered analyses. Most cross-sectional surveys also had low response rates [80, 91, 96, 97] or did not report either the response rate or the characteristics of non-respondents [66, 70, 78, 83,84,85, 87, 89, 90, 92, 93, 95, 98,99,100, 102]. Three cohort studies did not provide information on loss to follow-up [71, 86, 101], posing the risk of attrition bias. Six cohort studies had overlapping or ambiguous intervals over which diabetes and cancer screening status were determined [71, 72, 74, 76, 86, 101], which raises concerns around the exposure and outcome temporal order. Thirty-six studies controlled for either age or personal or family history of cancer [59, 65, 66, 70,71,72,73,74,75,76,77,78,79,80,81,82,83,84,89, 91–103] and 22 controlled for both [19,20,21,22,23,24,25,26,27,28, 30, 31, 35, 39, 40, 43, 44, 48, 50, 52, 54, 55].
Funnel plots for each cancer site indicate possible small study effects (ESM Figs. 2–4), suggesting that we cannot rule out the risk of publication bias. Low-precision studies showed lower screening participation in individuals with diabetes and a larger screening uptake gap between the groups, while higher-precision studies were closely and symmetrically distributed about the pooled effect size estimates.
Assessment of the exposure
Diabetes status was self-reported in 26 studies [59, 66, 70, 72, 77,78,79,80, 82,83,84,85, 88,89,90,91,92,93, 95,96,97,98,99,100, 102, 103], of which 17 considered ever-diagnosis [66, 70, 72, 78, 80, 83, 85, 90, 92, 93, 95,96,97,98,99, 102, 103], two considered current diagnosis [88, 100] and seven did not provide a look-back period [59, 77, 79, 82, 84, 89, 91]. The remaining studies defined diabetes up to 10 years before baseline using administrative data [65, 71, 73, 75, 81, 94], medical charts [74, 86, 101], records of prescription medications [76] and records of direct physical and laboratory examinations performed at the time of survey administration [87]. Two self-reported [78, 88] and four administrative data definitions [71, 73, 75, 94] were independently validated by healthcare professionals against medical charts [71, 73, 75, 78, 94] and responses to other survey questions [88].
Breast cancer screening
Breast cancer screening with a bilateral mammogram was defined using self-report in 17 studies [77, 78, 87,88,89,90,91,92,93, 95,96,97,98,99,100, 102, 103], administrative claims in seven studies [65, 71,72,73, 75, 76, 94] and medical records in three studies [74, 86, 101]. Most studies were conducted in age-eligible women and defined screening as receiving a mammogram within 1–3 years, which is consistent with clinical guidelines [27,28,29,30] (Table 2). To minimise inclusion of non-screening mammograms, studies excluded women with a history of breast cancer [65, 71,72,73,74,75, 78, 88, 95, 101], any cancer [94, 97, 100], mastectomy [71, 100, 101], recent abnormal mammogram [101] or mammogram performed after a recent breast cancer diagnosis [75]. Mammograms performed by invitation within organised programmes were considered as screening tests [65, 76, 88].
The prevalence of breast cancer screening ranged from 9.3% to 78.1% in women with diabetes and from 5.8% to 84.9% in women without diabetes. Adjusted ORs for breast cancer screening were reported by 19 studies [65, 71,72,73,74,75, 78, 86,87,88, 92,93,94,95,96,97,98, 101, 103] (Fig. 1). The remaining studies only reported the proportions of women screened in each group, due to the descriptive focus of the studies [76, 89, 90, 99, 100, 102], non-significant bivariate associations between diabetes and screening [91], or statistical model selection procedures [77]. One descriptive study [100] and 12 of the 19 analytical studies found that breast cancer screening participation was significantly lower in women with diabetes [65, 71, 73,74,75, 87, 88, 92,93,94, 97, 98].
The pooled OR for breast cancer screening uptake in women with diabetes relative to those without was 0.83 (95% CI 0.77, 0.90; 19 studies, 23 subgroups, I2 = 97%) (Fig. 1). Heterogeneity was partially explained by study designs and quality ratings; however, the effect size estimate remained robust in subgroup analyses across these factors (ESM Table 4). The likelihood of breast cancer screening in women with diabetes relative to those without was lower in studies conducted outside of the USA compared with those conducted in the USA [71, 72, 78, 86, 94,95,96,97,98, 101, 103] (outside USA: 0.78 [95% CI 0.69, 0.88], 8 studies, 8 subgroups, I2 = 99%; in USA: 0.89 [95% CI 0.84, 0.96], 11 studies, 15 subgroups, I2 = 54%).
Cervical cancer screening
Cervical cancer screening was determined using self-report in 17 studies [79, 80, 87,88,89,90,91,92,93, 95,96,97,98,99,100, 102, 103] and medical records in two studies [86, 101]. Consistent with clinical guidelines [31,32,33], most studies considered age-eligible women and defined screening as receipt of a Pap test within 2–3 years (Table 2). To approximate a screen-eligible population, some studies excluded women with a history of cervical cancer [88, 95, 101], any cancer [97, 100], hysterectomy [88, 89, 100, 101], or a recent abnormal Pap test [101].
The prevalence of cervical cancer screening ranged from 29.5% to 84.9% in women with diabetes and from 46.9% to 86.4% in women without diabetes. Seven studies did not report adjusted estimates due to the descriptive focus of the studies [89, 90, 99, 100, 102] or non-significant bivariate associations between diabetes and screening [79, 91]. Lower uptake of cervical cancer screening in women with diabetes was observed in four descriptive [79, 90, 99, 100] and six analytical studies [87, 92, 93, 97, 98, 103], while three descriptive [89, 91, 102] and six analytical studies [80, 86, 88, 95, 96, 101] found non-significant differences.
The pooled OR for cervical cancer screening uptake in women with diabetes relative to those without was 0.76 (95% CI 0.71, 0.81; 12 studies, 14 subgroups), with low heterogeneity (I2 = 0%) (Fig. 2). This finding was robust across subgroup analyses by study design and setting (ESM Table 4). Subgroup analyses by quality rating could not be performed, as all studies on cervical cancer screening were rated as lower quality.
Colorectal cancer screening
Colorectal cancer screening was determined using administrative data [81, 94] and medical records in two studies each [59, 101], and was self-reported in the remaining studies. Individuals were considered screened if they received a faecal or an endoscopic test, with faecal occult blood test (FOBT), flexible sigmoidoscopy and colonoscopy being the most frequently used tests. As recommended by clinical guidelines [34], screening intervals were 1–2 years for faecal tests [66, 70, 83,84,85, 95, 96, 99,100,101, 103] and 5–10 years for endoscopic tests [66, 70, 83,84,85, 96, 100, 101, 103], and target populations included adults over the age of 50 (Table 2). To minimise inclusion of non-screening tests, studies excluded individuals with a history of colorectal cancer [59, 66, 81,82,83, 95, 101], any cancer [94, 97, 100], inflammatory bowel disease [59, 81], colonic polyps or gastrointestinal bleeding [59], family history of colorectal cancer [59], hereditary polyposis/non-polyposis syndrome [59], colonoscopy before the age of 50 years [81], colectomy [81], colorectal cancer-related surgery [100], or recent abnormal screening results [101].
The prevalence of colorectal cancer screening ranged from 8.1% to 66.4% in individuals with diabetes and from 5.7% to 61.7% in individuals without diabetes. Twelve of the 18 studies reported adjusted ORs or PRs [59, 66, 70, 83, 84, 94,95,96,97,98, 101, 103]. The remaining studies had a descriptive focus [85, 99, 100, 102] or reported effect measures that could not be pooled with ORs [81, 82]. All four descriptive studies found that colorectal cancer screening was comparable between individuals with and without diabetes [85, 99, 100, 102]. The results of the analytical studies were mixed, with three studies showing significantly greater likelihood of screening in diabetes [70, 83, 103], five studies showing significantly lower likelihood of screening in those with diabetes [59, 81, 94, 97, 98] and six studies finding no significant difference [66, 82, 84, 95, 96, 101].
The pooled OR for colorectal cancer screening uptake in individuals with vs without diabetes was 0.95 (95% CI 0.86, 1.06; 12 studies, 16 subgroups, I2 = 90%) (Fig. 3). Heterogeneity was partially explained by differences in study design, participant sex and screening modalities (ESM Table 4). Cohort studies showed lower likelihood of screening in diabetes (0.77 [95% CI 0.70, 0.86], I2 = 0%), though this represented only four subgroups from three studies [59,94,101]. Women with diabetes were less likely to be screened compared with women without diabetes (0.86 [95% CI 0.77, 0.97]; 7 studies, 8 subgroups, I2 = 85%), while among men, no such association was observed. The analysis was robust across screening modality subgroups (FOBT vs flexible sigmoidoscopy or colonoscopy). We could not perform subgroup analyses by quality rating or study setting, as only two studies were rated to be of high quality [59, 94] and only one was conducted outside the USA [84]. Excluding each of these studies in sensitivity analyses did not meaningfully influence the results (ESM Table 4).