The aim of the present study was to determine the risk of lung cancer associated with cannabis smoking.
A case–control study of lung cancer in adults ≤55 yrs of age was conducted in eight district health boards in New Zealand. Cases were identified from the New Zealand Cancer Registry and hospital databases. Controls were randomly selected from the electoral roll, with frequency matching to cases in 5-yr age groups and district health boards. Interviewer-administered questionnaires were used to assess possible risk factors, including cannabis use. The relative risk of lung cancer associated with cannabis smoking was estimated by logistic regression.
In total, 79 cases of lung cancer and 324 controls were included in the study. The risk of lung cancer increased 8% (95% confidence interval (CI) 2–15) for each joint-yr of cannabis smoking, after adjustment for confounding variables including cigarette smoking, and 7% (95% CI 5–9) for each pack-yr of cigarette smoking, after adjustment for confounding variables including cannabis smoking. The highest tertile of cannabis use was associated with an increased risk of lung cancer (relative risk 5.7 (95% CI 1.5–21.6)), after adjustment for confounding variables including cigarette smoking.
In conclusion, the results of the present study indicate that long-term cannabis use increases the risk of lung cancer in young adults.
Cannabis smoking may have a greater potential than tobacco smoking to cause lung cancer 1–4. Cannabis smoke is qualitatively similar to tobacco smoke, although it contains up to twice the concentration of the carcinogenic polyaromatic hydrocarbons 1. Cannabis cigarettes are less densely packed than tobacco cigarettes, and tend to be smoked without filters 2 to a smaller butt size 3, leading to higher concentrations of smoke inhaled. Furthermore, smokers of cannabis inhale more deeply and hold their breath for longer 4, facilitating the deposition of the carcinogenic products in the lower respiratory tract. These factors are likely to be responsible for the five-fold greater absorption of carbon monoxide from a cannabis joint, compared with a tobacco cigarette of similar size despite similar carbon monoxide concentrations in the smoke inhaled 4. Several studies have demonstrated pre-cancerous histological 5, 6 and molecular 7 abnormalities in the respiratory tracts of cannabis smokers, and the carcinogenic effects of cannabis smoke have been demonstrated in vitro 8 and in different in vivo animal models 1, 9, 10. Conversely, there is also evidence that delta-9-tetrahydrocannabinol may have anti-carcinogenic effects 11–13.
Epidemiological evidence for an association between cannabis and lung cancer is limited and conflicting. Case series have suggested a causative role for cannabis in lung cancer in young adults 14, 15. The case–control studies published to date have shown both the presence 16–18 and absence 19 of an association, but have been limited by the inability to quantify use 16–18, confounding with combined cannabis and tobacco use 16–18, and studies being undertaken in populations in which use may have serious legal consequences resulting in potential information bias 16–19 and poor response rates 19.
New Zealand represents an ideal country in which to study the association between cannabis and respiratory tract cancer. New Zealand has a high rate of cannabis use 20, and cannabis is rarely mixed with tobacco within the joint 21, as is the custom in the UK 22. New Zealand has among the highest rates of lung cancer worldwide with the indigenous Maori population having the highest incidence of any ethnic group 23. These circumstances provided the opportunity to undertake a case–control study to investigate the association between lung cancer and cannabis use in young people.
Cases were patients with confirmed lung cancer aged ≤55 yrs at the time of diagnosis, identified from hospital databases and the New Zealand Cancer Registry between January 2001 and July 2005. Hospital databases were also used because a few clinical-only diagnoses of lung cancer are not received by the Cancer Registry 24. Cases were a mixture of prevalent and incident cases of lung cancer. Subjects were excluded if they had lung metastasis from a distant primary site other than lung, or a histological diagnosis of carcinoid or melanoma. Age at diagnosis, anatomical location of their malignancy and histological type were collected for cases. Controls without lung cancer were randomly selected from the electoral roll and frequency matched in 5-yr age groups and district health boards. Subjects came from eight district health board regions, serving both urban and rural populations. The eight district health boards serve together ∼1.8 million people, representing just under one-half of the total New Zealand population. The present study was approved by the regional ethics committees and each participant gave written informed consent. Patients with cancer of the head and neck were also interviewed, but will be reported separately.
Questionnaires were administered face-to-face by trained interviewers, usually at the home of the participant. Information on demographics (including ethnic group), smoking history, passive smoking exposure, recreational drug use, diet, occupation, income, education, alcohol consumption and family history of malignancy was collected. A family history of lung cancer was defined as having a sibling or parent with lung cancer. Occupations associated with a higher risk of lung cancer were identified from the literature and subjects were assigned a “duration at risk” value in years. Ethnicity was derived by priority coding of the responses into the following three groups: Maori, Pacific Islander and “other”. The highest level of educational attainment was recorded, as was income at diagnosis (or reference age). Alcohol consumption was calculated using a semi-quantitative score based on amount and frequency of consumption.
Subjects who reported having ever smoked ≥20 joints of cannabis were then asked to complete a more detailed exposure questionnaire regarding their cannabis smoking. This questionnaire obtained information about the age of starting cannabis use, the amount, frequency and duration of use, and the characteristics of their smoking. This information was collected for each period of their lives when pattern of use changed and was then summed to give an estimate of total lifetime use. If subjects smoked cannabis in a form other than a joint, e.g. pipes or bongs, they were asked to estimate the number of cannabis joints to which that would equate. This conversion allowed cannabis use for all participants to be quantified in joint-yrs of use, with 1 joint-yr being equivalent to 1 joint per day for 1 yr. Subjects who had smoked <20 and ≥20 cannabis joints in their lifetime were classified as nonsmokers and smokers of cannabis, respectively. A similar approach of determining lifetime use of cigarettes was employed to enable pack-yrs of cigarette smoking to be calculated, with 1 pack-yr being equivalent to 20 cigarettes per day for 1 yr. Subjects who reported smoking tobacco cigarettes occasionally but never daily, or daily at some stage in their life, were classified as nonsmokers and smokers of cigarettes, respectively. The questionnaire was piloted among ex-cannabis smokers.
Standard methods for analysis of case–control studies were used. The mean delay from diagnosis to interview was subtracted from the date of interview to calculate a reference date for duration of exposure for each control. Tertiles of cannabis use were determined by the marginal distribution of use for all subjects to reduce the chance of zero cell counts if just the control group was used. Relative risks (RRs) were estimated by calculating odds ratios by logistic regression and adjusted for confounding variables. Adjustment for age, joint-yrs of cannabis smoking and pack-yrs of cigarette smoking was made by including them as continuous variables in the regression models. The effects of categories of pack-yrs of cigarette smoking (quintiles of smoking for all subjects interviewed) and joint-yrs of cannabis smoking (tertiles of use for all subjects interviewed) were also assessed.
The RRs were also calculated based on cannabis use up to 5 yrs prior to diagnosis or a reference date in the controls, as exposure after that time was unlikely to have caused the malignancy. This 5-yr period was based on natural growth rates for lung cancer, in which the mean time from malignant change to diagnosis is at least 8 yrs for nonsmall cell lung cancers, and ∼3 yrs for small cell lung cancers 25, 26. The age at which cannabis smoking started was categorised, and the RR associated with starting at <16 yrs of age compared with ≥21 yrs was estimated. Various logistic regression models were fitted with potential confounders as continuous and categorical variables, and the estimates of RR and the confidence intervals (CIs) were not appreciably different from the results presented. Differences in Akaike's Information Criteria (AIC) were used to assess the linearity of the dose–response relationship of the risk of lung cancer after fitting parameters as continuous and categorical variables.
Assuming that 15% of the population smokes cannabis, a sample size of 75 cases and 300 controls had 80 and 90% power at a type 1 error rate of 5% to detect an odds ratio of lung cancer of 2.4 and 2.7, respectively.
A total of 102 eligible cases were contacted and invited for interview, of whom 79 (77%) agreed to participate. A total of 493 controls were contacted and invited for interview, and 324 (66%) agreed to participate. The frequency distribution of cases and controls interviewed for selected characteristics is shown in table 1⇓.
The 79 cases of lung cancer included 16 (20%) small cell and 63 (80%) nonsmall cell cancers. This is consistent with the established distribution of histological type seen in the general population 27. There were 39 (49%) female cases of lung cancer, similar to the female proportion (60%) of all lung cancer cases aged <55 yrs in New Zealand in 2002 28. In 2002 in New Zealand, 21% of cancer registrations among people <55 yrs of age occurred in Maori subjects compared with 23% of the cases interviewed. Also, there were 19 (24%) cases interviewed aged <45 yrs, similar to the proportion (23%) aged <45 yrs amongst all lung cancer cases aged <55 yrs 28. The controls (n = 324) who participated were similar to those who did not (n = 169) in terms of age (11 versus 13% <45 yrs) and sex (55 versus 51% female). However, eligible Maori control subjects were less likely to respond, with 9% of controls who participated being Maori compared with 15% of controls who did not participate.
The RR of lung cancer did not vary with age, due to cases and controls being frequency matched on 5-yr age group to improve the efficiency of the study. A family history of lung cancer was associated with an increased risk of lung cancer (RR = 3.9, 95% CI 1.8–8.4). There was no significant association between lung cancer risk and passive smoking, diet, occupation, income, educational level and alcohol use after adjustment for age, sex, ethnicity, cigarette smoking and a family history of lung cancer. The proportion of controls (aged 35–55 yrs) who had ever smoked cannabis, with age-adjustment for the age distribution of the general population was 36%, similar to the 40–52% reported amongst the younger 15–45 yr age group in New Zealand population surveys undertaken between 1990 and 2001 20.
While cannabis smoking (defined as lifetime use of ≥20 joints) was not associated with a significantly increased risk of lung cancer (table 2⇓), those with the highest tertile of use (>10.5 joint-yrs of exposure) had a significantly increased risk (RR 5.7 (95% CI 1.5–21.6)) after adjustment for age, sex, ethnicity, pack-yrs of cigarette smoking and a family history of lung cancer. When the analysis was restricted to non-Maori subjects, the RR was 5.9 (95% CI 1.2–28.5). Using the prevalence of the highest tertile of cannabis smoking of the controls, it was estimated that ∼5% of lung cancer in those aged ≤55 yrs in New Zealand may be attributable to cannabis smoking.
When joint-yrs of use were fitted as a continuous variable, thus providing greater statistical power than the assessment by tertile of use, a significant increasing risk of 8% with each joint-yr of use was found (RR = 1.08, 95% CI 1.02–1.15; table 3⇓). This estimate was unaltered when the analysis was restricted to non-Maori subjects. The difference in AIC between the model fitting joint-yrs of use as a continuous variable and that fitting tertiles of use was 2.23, indicating no clear discernment between a threshold and continuous effect of cannabis use and risk of lung cancer.
The strength of the association was maintained when cannabis use in the 5 yrs prior to diagnosis, or reference date for controls, was excluded (RR = 1.10, 95% CI 1.02–1.18; table 3⇑). A significant increase in the risk was also observed with increasing cigarette smoking, with a 7% increase in risk for each pack-yr of exposure (RR = 1.07, 95% CI 1.05–1.09), after adjustment for confounding variables including cannabis smoking. Therefore, the increased risk for each pack-yr of cigarette smoking was similar to that for each joint-yr of cannabis use.
Among users of cannabis no significant correlation between joint-yrs of use and age of onset of use was found (Pearson correlation coefficient 0.077, p = 0.56). Compared with subjects who started smoking cannabis aged ≥21 yrs, those that started under the age of 16 had a RR of lung cancer of 10.3 (95% CI 0.8–132) after adjustment for joint-yrs of cannabis use, pack-yrs of cigarette smoking, age, sex, ethnicity and a family history of lung cancer. After adjustment for joint-yrs of use, age, sex, ethnicity, a family history of lung cancer and pack-yrs of cigarette smoking, no significant decreasing trend in RR with years since last use was observed.
This population-based, case–control study provides evidence of a relationship between smoking cannabis and lung cancer in young adults. For each joint-yr of cannabis exposure the risk of lung cancer was estimated to increase by 8%.
There are a number of methodological considerations relevant to the interpretation of these findings. The present authors studied subjects aged ≤55 yrs due to published case series 14, 15, which suggested a strong association between cannabis use and lung cancer in young adults. Additionally, the lifetime exposure of older individuals would be expected to be much lower as they would have been older than the typical age for onset of use when the “epidemic” of cannabis use began in the 1960s. Due to the low incidence of lung cancer in this age group, representing <10% of all lung cancers 23, cases diagnosed up to 5 yrs before interview were included. No information from deceased cases was sought. If survival after diagnosis was different for users compared with nonusers of cannabis, this may have influenced the results obtained. Cases were identified from both the National Cancer Registry and from hospital outpatient and discharge databases to ensure case ascertainment was as complete as possible.
In the initial approach, no mention was made of the primary risk factor of interest to avoid recruitment bias with either the cases or the controls. To minimise response bias, the interviewer did not state the specific research hypothesis and took a detailed history of all well-known risk factors. Cannabis exposure was measured as joint-yrs of cannabis use, which combines both the intensity (amount and frequency) and duration of use. This approach follows the current convention for quantifying life-long cannabis consumption and recognises the evidence that the risk of lung cancer with cigarette smoking is related to both intensity and duration of use 29. Recall of the amount of cannabis smoked over a long period of time may have been difficult for some subjects; however, this is likely to have been similar for both cases and controls as subjects were not aware of the study hypothesis.
A population-based control group was used rather than a hospital-based control group as the latter is susceptible to significant bias due to the many medical conditions associated with cannabis use 30, 31. In recognition of the low incidence of lung cancer in the age group studied, four controls were studied for each case to increase the power of the study. Whilst eligible Maori control subjects were less likely to be interviewed, when confined to non-Maori subjects, the results were very similar to when they were included, suggesting that any differential control response by ethnicity was not a major confounder of the increased RR observed for lung cancer from cannabis use.
The major finding from the present study was that for each joint-yr of cannabis exposure, the risk of lung cancer increased by 8%, after adjustment for confounding variables including tobacco smoking. A major differential risk between cannabis and cigarette smoking was observed, with one joint of cannabis being similar to ∼20 cigarettes for risk of lung cancer. This is consistent with the observation that smoking “a few” cannabis joints a day causes similar histological changes in the tracheobronchial epithelium as smoking 20–30 tobacco cigarettes a day 32. It has also been reported that smoking two joints per day results in cytomorphological abnormalities in the sputum, similar to ∼30 cigarettes per day 33, 34. These differential risks are greater than the 1:5 dose ratio between cannabis and tobacco for carbon monoxide levels and the 1:3 dose ratio for amount of tar inhaled 4. This suggests that, as well as differences in smoking topography, in which cannabis joints are usually smoked without a filter 2, to a smaller butt size 3, using deeper and longer inhalation techniques 4, differences in chemical composition of cannabis and cigarette smoke may also be responsible for the differences in their lung cancer risks. In this regard, cannabis smoke has been shown to have greater concentrations of the carcinogenic polyaromatic hydrocarbons benz[a]pyrene and benz[a]anthracene than cigarette smoke 1.
The risk of lung cancer from cannabis use was restricted to the upper tertile of joint-yrs of use, with a 5.7-fold greater risk in those with >10.5 joint-yrs of cannabis use. However, it is unlikely that this represents a threshold effect, as a linear relationship has been clearly demonstrated between tobacco cigarette consumption and risk of lung cancer 35. The lack of an association in the lower tertiles may be due to the relatively small number of cannabis users in the study and the young age of subjects reducing the time available for high numbers of joint-yrs to accumulate, resulting in low levels of exposure (up to 1.39 joint-yrs for the lower tertile).
Further analysis was undertaken in which the risk of lung cancer was assessed for cannabis use up to 5 yrs prior to the diagnosis. This approach was based on evidence that in most cases of lung cancer, the duration between malignant change and diagnosis is >5 yrs 26. When cannabis use in the 5 yrs prior to diagnosis for the cases (and prior to the reference date for the controls) was excluded from the analysis the strength of the association was maintained, as would be expected if a causal association existed, with a 10% increase in risk for each joint-yr of exposure.
There was some suggestion that the risk of lung cancer may increase with earlier onset of cannabis use but the small number of subjects prevented more detailed assessment of this potential risk factor. However, such an association would be consistent with the evidence that the age of onset of tobacco smoking is a determinant of lung cancer risk 36, 37. Further case–control studies are needed to quantify the lung cancer risk associated with cannabis use, including the influence of the age of starting cannabis smoking, the dose–response relationship, and the dose equivalence with cigarette smoking.
In the young adults presently studied, the population attributable risk for cancer of the lung with cannabis smoking was estimated to be 5%. If any increased risk was maintained as these young people age, then a considerable burden from lung cancer due to cannabis smoking may occur in the future.
The present findings are consistent with the three North African case–control studies 16–18 that have reported a six- to eight-fold increased risk of lung cancer with cannabis smoking, although the lack of detailed smoking histories and the custom of mixing cannabis with tobacco may have contributed to the risks observed. In contrast, a large case–control study from California, USA, with an estimated participation rate in cases of only 39% reported no association between cannabis use and lung cancer 19. The controls in the Californian study were matched for neighbourhood, which may have made detection of an association less likely, as cannabis use is likely to be similar within distinct neighbourhoods. This may have contributed to the higher rates of cannabis use in the controls than previously reported from California 38. Also, African-American people were less likely to have participated than other ethnic groups, suggesting significant selection bias may have occurred. A positive relationship between cannabis use and cigarette smoking was observed in the controls, but the opposite relationship was present in the lung cancer cases, which also suggests selection bias or differential reporting between cases and controls. The practice of mixing tobacco with cannabis in the joint appears to vary between populations and may contribute to the geographical variation in risk of lung cancer from cannabis use observed.
These studies, and the present study, highlight the difficulties inherent in undertaking epidemiological research of the effects of cannabis. While it is important to interpret the findings in the context of these limitations, the balance of evidence would suggest a positive association between cannabis and lung cancer. This issue is of major public health importance, due to the prevalent use of cannabis globally and lung cancer being responsible for over a million deaths in the world each year 39, 40. With the prevalence and mortality from lung cancer increasing, prevention by risk factor modification is of paramount importance. Major efforts are being made to reduce the prevalence of tobacco smoking 41. The findings of the present study suggest that these public health programmes may need to include greater initiatives to reduce cannabis smoking and should be directed particularly at young people.
The Cannabis and Respiratory Disease Research Group
Executive Steering Committee: S. Aldington, M. Harwood, A. Pritchard, G. Robinson and R. Beasley (Medical Research Institute of New Zealand, Wellington, New Zealand); B. Cox (University of Otago, Dunedin, New Zealand); M. Weatherall (University of Otago Wellington, Wellington, New Zealand); L. Beckert (Christchurch Hospital, Christchurch, New Zealand); and A. Hansell (Imperial College of Science, Technology and Medicine, London, UK).
Regional Coordinators: M. Tweed, B. Mahon (Wellington Hospital, Wellington, New Zealand); L. Beckert, M. Campbell (Christchurch Hospital, Christchurch, New Zealand); MJ. Sneyd (University of Otago, Dunedin, New Zealand); R. Armstrong, C. Crawford (Hawkes Bay Hospital, Hastings, New Zealand); A. Watson, A. Lobhan (Palmerston North Hospital, Palmerston North, New Zealand); N. Graham (Tauranga Hospital, Tauranga, New Zealand); S. Holt (Research Review, Tauranga, New Zealand); J. McLachlan, P. Swann (Waikato Hospital, Hamilton, New Zealand); S. Tan (Hutt Hospital, Lower Hutt, New Zealand); G. Lear, N. Sheikh (Gisborne Hospital, Gisborne, New Zealand).
Funding was provided by The New Zealand Ministry of Health, The Hawke's Bay Medical Research Foundation. B. Cox was funded by the Director's Cancer Research Trust. A. Hansell is a Wellcome Trust Intermediate Clinical Fellow supported by grant number 075883. The funding bodies had no role in the design, data analysis or drafting of the manuscript.
Statement of interest
A statement of interest for this study can be found at www.erj.ersjournals.com/misc/statements.shtml
For editorial comments see page 227.
- Received May 31, 2007.
- Accepted August 21, 2007.
- © ERS Journals Ltd