Background:

The higher incidence of non–Hodgkin lymphoma (NHL) in males is not well understood. Although reactive oxygen species (ROS) have been implicated as causes of NHL, they cannot be measured directly in archived blood.

Methods:

We performed untargeted adductomics of stable ROS adducts in human serum albumin (HSA) from 67 incident NHL cases and 82 matched controls from the European Prospective Investigation into Cancer and Nutrition-Italy cohort. Regression and classification methods were employed to select features associated with NHL in all subjects and in males and females separately.

Results:

Sixty seven HSA-adduct features were quantified by liquid chromatography–high-resolution mass spectrometry at Cys34 (n = 55) and Lys525 (n = 12). Three features were selected for association with NHL in all subjects, while seven were selected for males and five for females with minimal overlap. Two selected features were more abundant in cases and seven in controls, suggesting that altered homeostasis of ROS may affect NHL incidence. Heat maps revealed differential clustering of features between sexes, suggesting differences in operative pathways.

Conclusions:

Adduct clusters dominated by Cys34 oxidation products and disulfides further implicate ROS and redox biology in the etiology of NHL. Sex differences in dietary and alcohol consumption also help to explain the limited overlap of feature selection between sexes. Intriguingly, a disulfide of methanethiol from enteric microbial metabolism was more abundant in male cases, thereby implicating microbial translocation as a potential contributor to NHL in males.

Impact:

Only two of the ROS adducts associated with NHL overlapped between sexes and one adduct implicates microbial translocation as a risk factor.

This article is featured in Selected Articles from This Issue, p. 1125

The non–Hodgkin lymphomas (NHL) comprise a group of malignancies derived primarily from B and T cells in lymphoid tissue. According to the Italian Association of Cancer Registries and the European Cancer Information System, NHL accounts for approximately 3% of all cancers in Italy with estimated 2020 incidences of 7,000 cases in males and 6,200 in females (1). From the 1970s to 1990s, the age-adjusted incidence of NHL in Italy increased by 3% to 4% per year and then stabilized in the 2000s (2), and similar trends were observed in other westernized countries (3). Age-standardized incidence rates varied worldwide from 4 to 19 per 100,000 males and 3 to 12 per 100,000 females, with the higher rates observed in westernized countries (3, 4).

The most prominent risk factor for NHL is immune deficiency—whether congenital or acquired from infections—with incidence rates among immuno-compromised individuals being many times that of the general population (5). Although relative NHL risks of 100 or more have been reported for individuals infected with HIV, more modest risks have been associated with diverse bacterial and viral infections [reviewed by (4)], e.g., a relative risk of 3.59 has been reported following chronic infection with hepatitis-C virus (6).

Infections activate phagocytic cells that release reactive oxygen species (ROS) to kill foreign organisms (7). Yet, ROS are generated naturally, e.g., by mitochondrial membranes in cells and via activation of NADPH oxidases in cytosol, and are detoxified by antioxidants under homeostasis. However, excessive production of ROS can overwhelm natural defenses and promote a cascade of events leading to metastatic cancers (8). The hypothesis that ROS are mechanistically linked to NHL is supported by increased risks with polymorphisms in oxidative-stress genes (9, 10) and type 2 diabetes mellitus (11), and by reduced risks with intake of dietary antioxidants (12, 13).

Because ROS cannot be measured in archived blood, investigators have studied their stable adducts with nucleophilic loci of blood proteins, particularly Cys34 of human serum albumin (HSA), which is the dominant scavenger of ROS in the interstitial space (14). Not only does Cys34 react directly with ROS, oxidation of its free sulfhydryl group to the unstable sulfenic acid (Cys34-SOH) leads to mixed-Cys34 disulfides of circulating thiols, including cysteine, glutathione and its precursors, glutamyl cysteine (GluCys) and cysteinyl glycine (CysGly), that are sentinels of redox biology (15, 16).

We developed an adductomics pipeline that employs nano-liquid chromatography–high-resolution mass spectrometry (nLC-HRMSMS) to measure all detectable Cys34 adducts in tryptic digests of human serum/plasma, which yield the triply-charged T3 peptide (21ALVLIAFAQYLQQC34PFEDHVK41, m/z 811.7593) and its modifications (17). Previous applications of Cys34 adductomics for cancer etiology employed archived serum from incident cases of colorectal cancer (18) and lung cancer (19) and matched controls from the Italian subset of the European Prospective Investigation into Cancer and Nutrition (EPIC-Italy), a cohort of healthy European adults enrolled between 1992 and 2000 (20). Those investigations found associations between adducts and cancer incidence up to 14 years prior to diagnosis and added mechanistic insights. A third application analyzed HSA from neonatal blood spots in childhood leukemia cases and matched controls and reported associations between adducts and incident cases of acute lymphoblastic and myeloid leukemias (21).

Because not all ROS react with Cys34, we recently extended our HSA-adductomics pipeline to include ε-amino modifications to Lys525, a hotspot for adduction of glycation end products and Schiff bases (22, 23). The combined Cys34/Lys525 pipeline interrogates modifications to both the T3 peptide and the doubly charged miscleaved Lys525 peptide (525KQTALVELVK534, m/z 564.8529). Here we report the first application of the Cys34/Lys525 pipeline to cancer etiology, using incident NHL cases and matched controls from the EPIC-Italy cohort. We conducted this exploratory study to discover adducts that discriminate for NHL incidence, with particular emphasis on sex differences and potential roles played by ROS and redox biology.

Cases and controls

Serum specimens from 67 incident cases of NHL (59 B-cell and 8 T-cell cases tabulated in Supplementary Table S1) and 82 controls were obtained from the EPIC-Italy cohort of 47,749 volunteers recruited in five centers in Italy between 1993 and 1998 (24). Written informed consent was obtained from all participants and the study was conducted in accordance with the World Medical Association Declaration of Helsinki. The study protocol was approved by an institutional review board of the Human Genetics Foundation (Turin, Italy). Participants were followed-up from the date of entry in the cohort until the occurrence of any cancer (except nonmelanoma skin cancer), death, emigration, or end of follow-up (between 2009 and 2014, depending on the center). NHL cases were identified through linkage with cancer and mortality registries by the morphology codes morphology 967–972 of the International Classification of Diseases (ICD-O-2). Controls from the cohort were matched to cases (1:1) by age, year and season of enrollment, and sex. After removal of 15 cases due to misclassified cancer type or missing covariate data, the corresponding 15 controls were retained in the analyses for feature selection. Information about diet, body mass index (BMI) and lifestyle factors were collected with questionnaires [including food frequency questionnaires (FFQ); ref. 25]. Table 1 lists summary statistics for the NHL cases and controls and selected covariates based on previous associations with NHL risk (4, 12, 13, 26). Across our subjects, no evidence of significant differences between NHL cases and controls were observed (nominal P values ≥ 0.23; Table 1). Table 1 also provides statistics for time (from recruitment) to case diagnosis (ttd, days).

Table 1.

Summary statistics for covariates included with NHL cases and controls.

VariableCases (n = 67)Controls (n = 82)P valuea
Sex Male 23 Male 32 0.67 
 Female 44 Female 50  
BMI (kg/m2Min 19.84 Min 15.53 0.63 
 Mean 26.42 Mean 25.76  
 Median 25.69 Median 26.06  
 Max 36.59 Max 36.16  
Alcohol consumption (g/d) Min Min 0.38 
 Mean 12.45 Mean 15.35  
 Median 5.13 Median 8.78  
 Max 64.78 Max 78.98  
Smoking status Yes 32 Yes 41 0.34 
 Ex 17 Ex 28  
 No 16 No 13  
Meat consumption (g/d) Min Min 10.4 0.40 
 Mean 108.9 Mean 114.1  
 Median 100.6 Median 105.3  
 Max 348.0 Max 350.5  
Physical activityb 17 22 0.67 
 23 29  
 17 16  
 15  
Age at recruitment (years) Min 40 Min 39 1.00 
 Mean 54.21 Mean 5,417  
 Median 54 Median 53  
 Max 74 Max 75  
Calorie consumption (kCal/d) Min 1,048 Min 1,021 0.64 
 Mean 2,269 Mean 2,323  
 Median 2,051 Median 2,110  
 Max 4,571 Max 5,727  
Leafy vegetable consumption (g/d) Min Min 0.3 0.51 
 Mean 35.22 Mean 36.06  
 Median 26.60 Median 26.75  
 Max 121.9 Max 138.3  
Fruiting vegetable consumption (g/d) Min 13.5 Min 9.6 0.43 
 Mean 76.24 Mean 70.18  
 Median 69.30 Median 66.65  
 Max 195.0 Max 202.8  
Root vegetable consumption (g/d) Min Min 0.55 
 Mean 15.09 Mean 15.75  
 Median 8.60 Median 8.85  
 Max 216.7 Max 127.8  
Cabbage consumption (g/d) Min Min 0.54 
 Mean 6.02 Mean 5.09  
 Median 3.80 Median 3.50  
 Max 29.6 Max 40.5  
Stalk vegetable and sprouts consumption (g/d) Min 0.3 Min 0.1 0.50 
 Mean 14.61 Mean 12.49  
 Median 12.3 Median 9.8  
 Max 54.5 Max 41.0  
Mixed vegetable consumption (g/d) Min Min 0.23 
 Mean 4.74 Mean 4.73  
 Median 1.1 Median 2.05  
 Max 94.8 Max 126.1  
Fruit consumption (g/d) Min 41.3 Min 27.5 0.26 
 Mean 331.6 Mean 346.1  
 Median 260.9 Median 320.6  
 Max 1,057 Max 894.6  
Nut and seed consumption (g/d) Min Min 0.27 
 Mean 1.16 Mean 1.24  
 Median 0.3 Median 0.3  
 Max 8.5 Max 14.3  
Time to diagnosis (days) Min 45    
 Mean 2,010    
 Median 2,005    
 Max 3,721    
VariableCases (n = 67)Controls (n = 82)P valuea
Sex Male 23 Male 32 0.67 
 Female 44 Female 50  
BMI (kg/m2Min 19.84 Min 15.53 0.63 
 Mean 26.42 Mean 25.76  
 Median 25.69 Median 26.06  
 Max 36.59 Max 36.16  
Alcohol consumption (g/d) Min Min 0.38 
 Mean 12.45 Mean 15.35  
 Median 5.13 Median 8.78  
 Max 64.78 Max 78.98  
Smoking status Yes 32 Yes 41 0.34 
 Ex 17 Ex 28  
 No 16 No 13  
Meat consumption (g/d) Min Min 10.4 0.40 
 Mean 108.9 Mean 114.1  
 Median 100.6 Median 105.3  
 Max 348.0 Max 350.5  
Physical activityb 17 22 0.67 
 23 29  
 17 16  
 15  
Age at recruitment (years) Min 40 Min 39 1.00 
 Mean 54.21 Mean 5,417  
 Median 54 Median 53  
 Max 74 Max 75  
Calorie consumption (kCal/d) Min 1,048 Min 1,021 0.64 
 Mean 2,269 Mean 2,323  
 Median 2,051 Median 2,110  
 Max 4,571 Max 5,727  
Leafy vegetable consumption (g/d) Min Min 0.3 0.51 
 Mean 35.22 Mean 36.06  
 Median 26.60 Median 26.75  
 Max 121.9 Max 138.3  
Fruiting vegetable consumption (g/d) Min 13.5 Min 9.6 0.43 
 Mean 76.24 Mean 70.18  
 Median 69.30 Median 66.65  
 Max 195.0 Max 202.8  
Root vegetable consumption (g/d) Min Min 0.55 
 Mean 15.09 Mean 15.75  
 Median 8.60 Median 8.85  
 Max 216.7 Max 127.8  
Cabbage consumption (g/d) Min Min 0.54 
 Mean 6.02 Mean 5.09  
 Median 3.80 Median 3.50  
 Max 29.6 Max 40.5  
Stalk vegetable and sprouts consumption (g/d) Min 0.3 Min 0.1 0.50 
 Mean 14.61 Mean 12.49  
 Median 12.3 Median 9.8  
 Max 54.5 Max 41.0  
Mixed vegetable consumption (g/d) Min Min 0.23 
 Mean 4.74 Mean 4.73  
 Median 1.1 Median 2.05  
 Max 94.8 Max 126.1  
Fruit consumption (g/d) Min 41.3 Min 27.5 0.26 
 Mean 331.6 Mean 346.1  
 Median 260.9 Median 320.6  
 Max 1,057 Max 894.6  
Nut and seed consumption (g/d) Min Min 0.27 
 Mean 1.16 Mean 1.24  
 Median 0.3 Median 0.3  
 Max 8.5 Max 14.3  
Time to diagnosis (days) Min 45    
 Mean 2,010    
 Median 2,005    
 Max 3,721    

aP values were computed with χ2 statistics for categorical variables and with Wilcoxon-rank sum tests for continuous variables.

bFor definitions and validation of physical activity see (48).

Laboratory analysis and data acquisition

Serum samples had been stored in liquid nitrogen for approximately 20 to 25 years prior to shipment to our laboratory where they were maintained at −80°C for a few months prior to analysis in 2018. Laboratory investigators were blinded with regard to disease status except that case/control pairs were analyzed in the same daily analytical batch and in random order to reduce effects of technical variation. Sample processing and analysis by nLC-HRMSMS were performed with duplicate injections as previously described (22, 23) and elaborated in Supplementary Methods S1. Briefly, after digesting HSA with trypsin, an isotopically labeled and iodoacetamide-modified T3 peptide (IAA-iT3) was added as an internal standard to normalize data for instrument performance. One microliter of each digest was then analyzed by nLC-HRMSMS to locate spectra from the T3 and Lys525 peptides (17, 22). The corresponding precursor ions were extracted to obtain a monoisotopic mass (MIM) for each peptide feature (hereafter simply ‘feature’) and assign accurate masses. To normalize peak areas for the amount of HSA in each sample, the MIM was also extracted for the robust HSA peptide 42LVNEVTEFAK51 (m/z = 575.3111), adjacent to the T3 peptide and referred to as the housekeeping peptide (HKP). The peak area ratio (PAR) of the adduct peak to that of the HKP is a robust measure of the adduct concentration (17). Peak picking and integration were performed with the average MIMs and retention times. Added masses relative to the Cys34 thiolate ion and the Lys525 peptide were estimated as described in Supplementary Methods S1. Putative adducts were annotated on the basis of a combination of retention time, accurate mass, elemental composition, database searches and available reference standards.

Statistical analysis

Data consist of nLC-HRMSMS peak areas for 57 Cys34-containing features and 12 Lys525-containing features from 148 samples analyzed with duplicate injections and one with a single injection (n = 297). Duplicate injections are used to estimate the amount of technical variation in nLC-HRMSMS analysis and averaging them lessens the impact of this source of variability. As previously described (18), peak areas were log-transformed and intraclass correlation coefficients (ICC) and coefficients of variation (CV) were estimated using a one-way random effects model where the log-abundance of the feature was the subject-specific effect and duplicate injections were sample-specific effects. Using an empirical ICC cutoff of > 0.2 to remove features with large proportions of technical variation resulted in removal of five features, leaving 62 for further analysis. For each feature, log-abundances from 148 duplicate injections were averaged, ignoring missing values, and those with more than 30% missing values were removed. This resulted in the additional removal of 27 features, leaving 35 for further analysis. When values were missing from both duplicate injections, missing values were imputed using k-nearest-neighbor imputation with the number of neighboring features set to five. The scone package (https://rdrr.io/bioc/scone/) was used to select a normalization scheme with inputs consisting of the imputed abundance matrix, the analytical-batch variable, a binary case/control variable, and the matrix of sample-level quality control (QC) measures (i.e., HKP abundance, internal standard abundance and sample run order). On the basis of performance measures returned by scone, the data were normalized using upper-quartile scaling while adjusting for case/control status, batch, and all three principal components of the QC matrix.

Statistical analyses of the normalized data were performed in the R environment as previously described (18, 21). To capture associations between features and case/control status for hypothesis generation, features were selected using an ensemble approach based on multivariate linear regression, regularized logistic regression (LASSO), and Random Forest. First, the following linear regression model was used for a given logged and scaled feature abundance Y in the ith subject:
where: case/control denotes binary status, Q represents the matrix of QC principal components, sex and age (at recruitment) are self-explanatory, and batch is the analytical sample batch. Features were ranked by their nominal unadjusted P values for testing the null hypothesis that the case/control coefficient (β1) is zero using a t test, and the case/control fold-change (FC) was estimated as exp(⁠|${\hat{\beta }}_1$|⁠). Second, a LASSO model was fit to normalized feature abundances over 500 bootstrapped datasets, with case/control status as the outcome variable and the following independent variables: normalized logged abundances for all 35 features, and the covariates age and sex. The percentage of times that each feature was selected by LASSO was used to rank its association with NHL. The same input was given to Random Forest to rank features by their mean decreases in Gini index. Features highly ranked by concordance plots for both linear regression nominal P value and LASSO were joined with those of high importance from Random Forest, to provide additional evidence of associations with NHL, including non-linear associations. Given prior evidence that NHL incidence was consistently greater in males, feature selection was repeated separately for males and females.

Correlations between normalized feature abundances were displayed with agglomerative hierarchical clustering using complete linkage of Spearman correlation values (‘superheat’ function in R from the superheat package). Associations between selected features and covariates (smoking, BMI, caloric intake, consumption of meat, vegetables and alcohol, physical activity, and age) were further ranked with Random Forest.

Because NHL cases and matched controls were evaluated up to 21 years after recruitment, we used permutation tests to check for associations between relative adduct abundance (case/matched control) and days from recruitment to diagnosis (ttd) to differentiate between potentially causal effects or reactive effects of disease progression (reverse causality; refs. 18, 27, 28). This was done by randomly permuting the ttd of a given case and the log(FC) 10,000 times (thereby breaking any association between the two), each time recording the slope of the best fit line when regressing log(FC) on ttd. The P value reported is the percentage of the 10,000 random permutations that the absolute value of the estimated slope was greater than or equal to the absolute value estimated using the observed data. If a significant linear trend in log(FC) for a given feature was detected with increasing days to diagnosis, the adduct feature was considered as potentially reactive.

Data availability

The data generated in this study are available upon request from the corresponding author.

The 57 Cys34 and 12 Lys525 features are listed in Supplementary Tables S2A and S2B, respectively. For each feature, the LC retention time, observed and theoretical MIMs and the corresponding mass deviation (Δmass), accurate mass, added mass and elemental composition are shown along with the annotation and PAR value. Supplementary Table S3 shows FCs and the nominal P values for testing the null hypothesis that the case/control coefficient (β1) is zero using a t test for both the unstratified and sex-stratified data. Case–control–fold changes were both positive and negative, indicating that some features were more abundant in cases and others in controls, respectively. Supplementary Table S4 shows the within- and between-subject variance components from the random effects model of each feature and the corresponding values of the ICC (median = 0.753) and CV (median = 0.337). Forty seven of the 67 detected features have been reported previously in our laboratory, with citations noted as footnotes in Supplementary Tables S2A and S2B.

Supplementary Fig. S1A–S1C, S1D–S1F, and S1G–S1I show the results of feature selection for all subjects, males and females, respectively, and Table 2 combines the results to list features selected for associations with NHL. Altogether ten features satisfied the selection criteria based on multivariate linear regression plus LASSO and/or Random Forest: eight Cys34 adducts, i.e., 796.43 (Cys→Gly, males), 805.76 (Cys→oxoalanine/formylglycine, males), 816.43 (methylation, males and females), 822.42 (Cys34 sulfinic acid, males), 827.088 (methanethiol, males), 827.094 (Cys34S–(O)–O–CH3, all subjects and males), 835.11 (crotonaldehyde, females) and 894.44 (γ-GluCys, all subjects, males and females), and two Lys525 features, i.e., 580.85 (Lys525 oxidation product, females) and 578.32 (unknown, all subjects and females). Two of the three features selected from analyses of all subjects were heavily influenced by either males (827.094) or females (578.32). Eight of the ten selected features were more abundant in controls and two were more abundant in (male) cases.

Table 2.

Features selected by the ensemble pipeline for association with NHL. The boldface font indicates selection criteria that were satisfied. [Fold-change based on normalized and imputed data (FC); nominal p-value; bootstrap LASSO; Random Forest (RF)].

All subjectsMalesFemales
FeatureAnnotationFCP valueLASSORFFCP valueLASSORFFCP valueLASSORF
578.32 Unknown 0.892 0.034 Yes Yes 0.921 0.353 No No 0.887 0.083 Yes Yes 
580.85 Oxidation of Lys525 (+HO20.798 0.133 No No 0.913 0.713 No No 0.752 0.112 Yes No 
796.43 Cys34→Gly 0.893 0.054 No No 0.792 0.017 Yes Yes 0.960 0.581 No No 
805.76 Cys34→OA/FG 0.943 0.211 No No 0.822 0.022 Yes No 0.998 0.971 No No 
816.43 Methylation (at Glu37) 0.995 0.953 No No 1.204 0.136 Yes Yes 0.886 0.219 No Yes 
822.42 Cys34 sulfinic acid 0.958 0.468 No No 0.826 0.069 Yes No 1.063 0.388 No No 
827.088 Methanethiol 1.135 0.314 No No 1.392 0.127 Yes Yes 1.025 0.865 No No 
827.094 Cys34S–(O)–O–CH3 0.844 0.005 Yes Yes 0.735 0.005 Yes Yes 0.916 0.240 No No 
835.11 Crotonaldehyde 0.867 0.093 No No 1.032 0.804 No No 0.785 0.019 Yes Yes 
894.44 γ-GluCys 0.855 0.047 Yes Yes 0.710 0.029 Yes Yes 0.922 0.380 No Yes 
All subjectsMalesFemales
FeatureAnnotationFCP valueLASSORFFCP valueLASSORFFCP valueLASSORF
578.32 Unknown 0.892 0.034 Yes Yes 0.921 0.353 No No 0.887 0.083 Yes Yes 
580.85 Oxidation of Lys525 (+HO20.798 0.133 No No 0.913 0.713 No No 0.752 0.112 Yes No 
796.43 Cys34→Gly 0.893 0.054 No No 0.792 0.017 Yes Yes 0.960 0.581 No No 
805.76 Cys34→OA/FG 0.943 0.211 No No 0.822 0.022 Yes No 0.998 0.971 No No 
816.43 Methylation (at Glu37) 0.995 0.953 No No 1.204 0.136 Yes Yes 0.886 0.219 No Yes 
822.42 Cys34 sulfinic acid 0.958 0.468 No No 0.826 0.069 Yes No 1.063 0.388 No No 
827.088 Methanethiol 1.135 0.314 No No 1.392 0.127 Yes Yes 1.025 0.865 No No 
827.094 Cys34S–(O)–O–CH3 0.844 0.005 Yes Yes 0.735 0.005 Yes Yes 0.916 0.240 No No 
835.11 Crotonaldehyde 0.867 0.093 No No 1.032 0.804 No No 0.785 0.019 Yes Yes 
894.44 γ-GluCys 0.855 0.047 Yes Yes 0.710 0.029 Yes Yes 0.922 0.380 No Yes 

Abbreviation: OA/FG, oxoalanine/formyl glycine.

To determine whether the eight T-cell lymphomas substantially altered the results, we repeated data normalization, imputation and feature selection after excluding the T-cell cases (three males and five females). The results, summarized in Supplementary Table S5, are very similar to those in Table 2. Eleven features were selected (rather than ten), including the same seven in males and six (rather than five) in females, and four (rather than three) in all subjects. One new feature was selected in females, 647.34 (unknown) and 835.11 (crotonaldehyde) was now also selected in all subjects.

Heat maps presenting matrices of Spearman correlations between features and their corresponding clusters are shown in Fig. 1A and B for males and Fig. 2A and B for females, respectively. Clusters containing selected features (shown in red) provide clues regarding pathways towards peptide modifications associated with NHL, i.e., clusters C1-C3 for males and D1-D3 for females. Fig. 3A and B; Fig. 4A and B show Random Forest plots and the corresponding heat maps of the selected features and 15 covariates for males and females, respectively. For males, Fig. 3A shows that five selected features are ranked as more important by Random Forest than any covariate. Total calories and fruit have somewhat lesser importance by Random Forest while physical activity and smoking have the least importance. The corresponding heat map (Fig. 3B) shows that the five features in cluster E1 (796.43, 805.78, 822.42, 827.088, and 827.094) tend to be strongly negatively correlated with age, total calories and consumption of alcohol and meat (cluster E3) and to a lesser extent with leafy vegetables. In E2, feature 894.44 clusters with BMI, age and smoking and has a strong negative correlation with physical activity. Regarding females, Fig. 4A indicates that consumption of fruit and meat showed importance by Random Forest that was comparable with four of the selected features (578.32, 816.43, 894.44, and 835.11) while other covariates showed substantially less importance. The heat map (Fig. 4B) shows contrasting correlations of these four features with covariates where strong/moderate negative correlations are seen between 835.11 and 816.43 and smoking and root vegetables, and also between 894.44 and meat, physical activity and nuts and seeds, and between 578.32 and physical activity and fruiting vegetables.

Figure 1.

Heat map showing all features in MALE subjects (A) with clusters identified in (B). Features selected for association with NHL are highlighted in red.

Figure 1.

Heat map showing all features in MALE subjects (A) with clusters identified in (B). Features selected for association with NHL are highlighted in red.

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Figure 2.

Heat map showing all features in FEMALE subjects (A) with clusters identified in (B). Features selected for association with NHL are highlighted in red.

Figure 2.

Heat map showing all features in FEMALE subjects (A) with clusters identified in (B). Features selected for association with NHL are highlighted in red.

Close modal
Figure 3.

Variable importance of covariates and selected features as ranked by Random Forest in MALE subjects (A) and heat map showing the corresponding correlations (B).

Figure 3.

Variable importance of covariates and selected features as ranked by Random Forest in MALE subjects (A) and heat map showing the corresponding correlations (B).

Close modal
Figure 4.

Variable importance of covariates and selected features as ranked by Random Forest in FEMALE subjects (A) and heat map showing the corresponding correlations (B).

Figure 4.

Variable importance of covariates and selected features as ranked by Random Forest in FEMALE subjects (A) and heat map showing the corresponding correlations (B).

Close modal

To determine whether abundances of selected features may have resulted from disease progression (reverse causality) rather than their causal role in NHL, we examined the relationships between log(FCs) of adduct abundances of NHL case/control pairs and days from recruitment to diagnosis (ttd). Results are presented in Supplementary Fig. S2A and S2B as individual plots for the seven selected features in males and five in females, respectively. Of these nine features, only 816.43 (methylation) in male subjects had a sufficiently small P value for the regression coefficient (P = 0.0026) to suggest reverse causality (Supplementary Fig. S2A).

As with our previous adductomic investigations of colorectal cancer and childhood leukemia (18, 21), this study of incident NHL cases and controls relied on an ensemble of regression and classification methods to generate hypotheses about features for likely association with NHL, up to 11 years prior to diagnosis (Table 2). All seven of the T3-peptide features had previously been reported in humans (Supplementary Table S2A) suggesting that their reactive precursors, including ROS, represent common exposures and/or pathways that increase NHL risks. The two Lys525 features selected for association with NHL (578.32 and 580.85) had not previously been reported in the two prior studies that included modifications at that locus (Supplementary Table S2B).

Two interesting findings emerged (Table 2). First, only two of the nine selected features overlapped between males and females, supporting empirical evidence that NHL incidence differs substantially between sexes (3, 4). Indeed, if we had relied solely on analysis of all subjects, six of the nine selected features would have been missed. Second, seven of the nine selected features were more abundant in controls (FC range: 0.710–0.826), while only two were more abundant in (male) cases (FC: 1.204 and 1.392; Figs. 1B and 2B). This indicates that adduct features reflect both protective and detrimental effects on NHL incidence.

Focusing first on the features selected in male subjects, four were present in cluster C1, one in C2 and one in C3 (Fig. 1A). Cluster C1 contains products of sulfoxidation or oxidative cleavage of Cys34, including selected features: 796.43 (Cys→Gly, FC = 0.792), 822.42 (Cys34 sulfinic acid, FC = 0.826) and 827.094 (Cys34S–(O)–O–CH3, FC = 0.735). Inclusion of selected feature 827.088 (S-addition of methanethiol, FC = 1.392) in C1 is particularly intriguing because methanethiol is a product of microbial-human co-metabolism that is mediated by the gut microbiota via catabolism of methionine and/or methylation of hydrogen sulfide (29). Our previous investigation of colorectal cancer found elevated levels of 827.088 in incident cases (18), thereby implicating the gut microbiota as a colorectal cancer risk factor, consistent with formal hypotheses (30, 31). Here, a similar positive association of NHL with 827.088 years prior to diagnosis suggests that translocation of gut microbes to the circulation may increase NHL risk.

Microbial translocation from the gut to the circulation and the resulting immune activation in healthy humans can result from a host of factors, including gut microbial dysbiosis, viral infections, IgA deficiency, reduced bacterial clearance by the liver, and excessive alcohol consumption (32), and has been associated with B-cell NHL following HIV infection (33). The fact that 827.088 clusters in C1 with features representing Cys34 oxidation products suggests a possible pathway involving systemic inflammation induced by gut microbial translocation. Indeed, the Cys34 sulfinic and sulfonic acids (822.42 and 827.75, respectively) in C1 are recognized biomarkers of systemic inflammation that have been linked to several diseases and syndromes including type 2 diabetes mellitus (34, 35) [a risk factor for NHL (11)], kidney disease (36), liver disease and sepsis (37, 38), and hemodialysis (39).

Referring next to cluster C2, feature 894.44 (Cys34 disulfide of γ-GluCys) is less abundant in NHL cases (FC = 0.710). γ-GluCys is a precursor of GSH that is the predominant intracellular scavenger of ROS (40). Although our previous study of lung cancer found that lower abundance of 894.44 was associated with increased smoking intensity and pack-years of cigarette consumption (19), this adduct shows moderate positive correlation with smoking in this study (Fig. 3B). Membrane-bound γ-glutamyltranspeptidase catabolizes conversion of extracellular GSH to CysGly (another constituent of C2) that stimulates production of pro-oxidant species and is upregulated by depletion of intracellular GSH (41, 42). Thus, the high correlation in C2 between Cys34 disulfides of γ-GluCys (894.44) and CysGly (870.43) points to dysregulation of GSH metabolism in NHL cases. Interestingly, similar reductions in levels of 894.44 and 870.43, as well as that of the GSH adduct (913.45), were observed in smokers from the lung-cancer study (19) and also among nonsmoking Chinese females exposed to indoor effluents from coal combustion, a major source of ROS (43). It is also noteworthy that 827.088 (methanethiol) is negatively correlated with both 894.44 and 870.43, suggesting roles for microbial translocation in GSH metabolism and redox biology.

The large C3 cluster contains a mixture of Cys34 and Lys525 features, one of which was selected for association with NHL, i.e., 816.43 [816.43 (methylation of T3 at Glu 37), FC = 1.204]. The T3-methylation product 816.43 has been observed in all prior applications of our adductomics pipelines, including inconsistent associations with smoking (17, 19). Review of HRMSMS spectra for this investigation confirmed that Glu37 is the methylation site in the T3 peptide. As noted previously, the significant trend of 816.43 abundance with ttd in male subjects (Supplementary Fig. S2A) points to reverse causality and encourages investigation of 816.43 as an early biomarker of NHL, with lower abundance at diagnosis.

Turning now to features selected for association with NHL among females (Table 2), in addition to 816.43 and 894.44 (also selected in males) 835.11 (crotonaldehyde, FC = 0.785) has been reported previously (footnoted in Supplementary Table S2), while 578.32 (unknown, FC = 0.886) and 580.85 (Lys525 oxidation product) are novel to the current investigation. Crotonaldehyde is a reactive α, β-unsaturated aldehyde produced by ROS oxidation of membrane lipids (44), and we had previously found 835.11 to be elevated in colorectal cancer cases (18) as well as in incident cases of childhood acute lymphoblastic leukemia (21) and in workers exposed to benzene (45), a known human leukemogen and promoter of ROS that has been causally linked with NHL (46) and with autoimmune disease as a risk factor for NHL (47). Figure 2A shows that unknown feature 578.32 and the Lys525 oxidation product 580.85 cluster with each other and with unknown feature 587.31 (cluster D3). The fact that neither 578.32 and 580.85 nor 816.43 and 835.11 are appreciably correlated with the oxidation products in D2 that were favored in C1 for association with NHL in males (Fig. 1A) emphasizes differences in operative pathways between sexes. However, 894.44 (γ-GluCys adduct) is marginally negatively correlated the oxidation products in D2 (Fig. 2A), albeit much weaker than the corresponding correlations observed in males (Fig. 1A). Also 827.088 (methane thiol adduct) is moderately positively correlated with the D2 oxidation products suggesting possible influences of microbial translocation/systemic inflammation in females.

Analyses of covariates summarized in Figs. 3A and 4A indicate that calories (total energy) and consumption of fruit and meat were highly ranked for importance to NHL incidence by Random Forest in both sexes. In males, alcohol was also highly ranked whereas, in females, stalk vegetables and sprouts were highly ranked. In particular, three of the five features representing Cys34 oxidation products in cluster E1 of the male heat map (Fig. 3B: 796.43, 805.76, and 827.088) are all negatively correlated with intake of calories, alcohol and meat. A similar pattern is seen for features 816.43 and 835.31 in the female heat map (Fig. 4B), which are negatively correlated with intake of alcohol, meat and fruiting and root vegetables.

Figure 5 shows a Mean-Difference plot of the case/control ratios of median values of feature abundances for covariates by sex. Because deviations from the dashed line, representing equal ratios, indicate substantial differences between sexes, ratios for consumption of cabbage and root vegetables tend to be greater in females while those for calories and consumption of alcohol, fruit, meat, and mixed and leafy vegetables tend to be greater in males. These sex differences in dietary and alcohol consumption and the heat maps in Figs. 3B and 4B may help to explain the limited overlap of feature selection between males and females (Table 2). Also, the correlations between selected features and consumption of alcohol, meat and certain vegetables are interesting when considering that these same covariates are recognized risk factors for NHL (4, 13).

Figure 5.

Mean-Difference plot of median values of case/control ratios for covariates by sex. The y-axis shows the case/control ratio of median values in males minus the case/control ratio of median values in females. The x-axis shows the mean of these two quantities. The dashed line indicates no difference in the ratio between males and females.

Figure 5.

Mean-Difference plot of median values of case/control ratios for covariates by sex. The y-axis shows the case/control ratio of median values in males minus the case/control ratio of median values in females. The x-axis shows the mean of these two quantities. The dashed line indicates no difference in the ratio between males and females.

Close modal

Perhaps our most provocative finding is evidence that the methanethiol adduct (827.088) is elevated in male NHL cases. This biomarker of enteric microbial metabolism was previously found to be elevated in incident colorectal cancer cases, where translocation of enteric bacteria into colonic mucosa and the resulting inflammatory response hypothetically contributed to localized tumors (18). Extending this hypothesis to NHL implies that microbial translocation from the gut results in systemic release of microbes and the resulting inflammation/ROS that can transform circulating lymphocytes and/or promote cancers throughout the body. Furthermore, associations between 827.088 and intake of total calories, alcohol, meat, and leafy vegetables suggest that prior reports of NHL associations with intake of alcohol, meat and dietary constituents (4) may involve microbial pathways. Follow-up is needed to confirm this finding with additional data from prospective cohorts, preferably in conjunction with fecal metagenomics to determine whether gut microbial dysbiosis may be involved and with screening for immune activation.

Our study has some strengths. First, the adductomics assay provides direct evidence of the disposition of ROS in the interstitial space during the month preceding phlebotomy and thus is highly relevant to ROS-induction of NHL. Second, our hypothesis-free design and ensemble of regression/classification methods permitted unbiased selection of adducts for associations with NHL. Third, expanding the Cys34 adductomics pipeline to Lys525 extended the range of adducts and their underlying chemistries, and included two selected features (578.32 and 580.85). And third, the high quality of serum samples from the EPIC-Italy cohort collected up to 11 years prior to diagnosis reduced the potential for reverse causality.

There are also weaknesses. The sample size was small, particularly after stratification by sex (Table 1) and results will require validation. Although storage of biological specimens for decades can produce artifacts, specimens were stored (for 20–25 years) in liquid nitrogen, and cases and controls were matched by year of enrollment to minimize potential storage effects. While four selected adducts were confirmed with synthetic standards (827.088, 827.094, 835.11, and 894.44), annotations of the others were based on elemental composition and should be regarded as putative. Because HSA adducts have a residence time of one month in humans, adduct levels measured in blood collected at recruitment may not accurately reflect those in following months or years. Likewise, given the seasonality of the Italian diet, correlations between adduct levels and dietary covariates collected by FFQ should be interpreted skeptically. Another limitation was our inability to examine connections between adducts and advanced neoplasms (precursors of NHL) for advanced stage vs. early stage cancers.

In summary, we used untargeted adductomics to detect 68 adduct features in HSA from 67 incident NHL cases and 82 controls, of which nine were selected for association (seven in males and five in females), with three selected in both sexes. The minimal overlap among selected features between males and females reinforces well-known sex differences in NHL risk. In male subjects, decreased abundances of several features representing oxidative pathways as well as γ-GluCys (894.44), a precursor of GSH, add weight to findings that long-term oxidative stress can lead to dysregulation of redox biology. Also, the increased abundance of the methanethiol adduct (827.088) and its correlation with Cys34 oxidation products in males implicates enteric microbial translocation and the resulting systemic inflammation as a potential pathway for NHL.

P. Imani reports grants from NIH; and grants from NIH during the conduct of the study. S.M. Rappaport reports grants from NIH; and grants from European Commission during the conduct of the study. No disclosures were reported by the other authors.

H. Grigoryan: Data curation, formal analysis, investigation, methodology, writing–original draft. P. Imani: Data curation, software, formal analysis, methodology, writing–original draft. C. Sacerdote: Resources, data curation, writing–review and editing. G. Masala: Resources, data curation, writing–review and editing. S. Grioni: Resources, data curation. R. Tumino: Resources, data curation. P. Chiodini: Resources, data curation. S. Dudoit: Conceptualization, software, supervision, funding acquisition, methodology, writing–review and editing. P. Vineis: Conceptualization, resources, funding acquisition, writing–review and editing. S.M. Rappaport: Conceptualization, resources, supervision, funding acquisition, writing–original draft, project administration, writing–review and editing.

Financial support for this work was provided from the NIH through grants R33CA191159 from the NCI (to S. Rappaport, S. Dudoit) and P42ES04705 from the National Institute for Environmental Health Sciences (to S. Rappaport) and grant agreement 308610-FP7 from the European Commission (Project Exposomics; to P. Vineis, S. Rappaport). The authors appreciate the helpful comments of Christine Skibola who reviewed a draft of the manuscript.

The publication costs of this article were defrayed in part by the payment of publication fees. Therefore, and solely to indicate this fact, this article is hereby marked “advertisement” in accordance with 18 USC section 1734.

Note: Supplementary data for this article are available at Cancer Epidemiology, Biomarkers & Prevention Online (http://cebp.aacrjournals.org/).

1.
ECIS - European Cancer Information System. 2023 Estimates of cancer incidence and mortality in 2020, for all countries
. In
ECIS - European Cancer Information System
.
European Union
.
Available from:
<https://ecis.jrc.ec.europa.eu>.
2.
Miranda-Filho
A
,
Pineros
M
,
Znaor
A
,
Marcos-Gragera
R
,
Steliarova-Foucher
E
,
Bray
F
.
Global patterns and trends in the incidence of non–Hodgkin lymphoma
.
Cancer Causes Control
2019
;
30
:
489
99
.
3.
Muller
AM
,
Ihorst
G
,
Mertelsmann
R
,
Engelhardt
M
.
Epidemiology of non–Hodgkin's lymphoma (NHL): trends, geographic distribution, and etiology
.
Ann Hematol
2005
;
84
:
1
12
.
4.
Alexander
DD
,
Mink
PJ
,
Adami
HO
,
Chang
ET
,
Cole
P
,
Mandel
JS
, et al
.
The non–Hodgkin lymphomas: a review of the epidemiologic literature
.
Int J Cancer
2007
;
120
Suppl 12
:
1
39
.
5.
Grulich
AE
,
Vajdic
CM
,
Cozen
W
.
Altered immunity as a risk factor for non–Hodgkin lymphoma
.
Cancer Epidemiol Biomarkers Prev
2007
;
16
:
405
8
.
6.
Pol
S
,
Vallet-Pichard
A
,
Hermine
O
.
Extrahepatic cancers and chronic HCV infection
.
Nat Rev Gastroenterol Hepatol
2018
;
15
:
283
90
.
7.
Halliwell
B
.
Free radicals, antioxidants, and human disease: curiosity, cause, or consequence?
Lancet
1994
;
344
:
721
4
.
8.
Liou
GY
,
Storz
P
.
Reactive oxygen species in cancer
.
Free Radic Res
2010
;
44
:
479
96
.
9.
Lan
Q
,
Zheng
T
,
Shen
M
,
Zhang
Y
,
Wang
SS
,
Zahm
SH
, et al
.
Genetic polymorphisms in the oxidative stress pathway and susceptibility to non–Hodgkin lymphoma
.
Hum Genet
2007
;
121
:
161
8
.
10.
Wang
SS
,
Davis
S
,
Cerhan
JR
,
Hartge
P
,
Severson
RK
,
Cozen
W
, et al
.
Polymorphisms in oxidative stress genes and risk for non–Hodgkin lymphoma
.
Carcinogenesis
2006
;
27
:
1828
34
.
11.
Castillo
JJ
,
Mull
N
,
Reagan
JL
,
Nemr
S
,
Mitri
J
.
Increased incidence of non–Hodgkin lymphoma, leukemia, and myeloma in patients with diabetes mellitus type 2: a meta-analysis of observational studies
.
Blood
2012
;
119
:
4845
50
.
12.
Holtan
SG
,
O'Connor
HM
,
Fredericksen
ZS
,
Liebow
M
,
Thompson
CA
,
Macon
WR
, et al
.
Food-frequency questionnaire-based estimates of total antioxidant capacity and risk of non–Hodgkin lymphoma
.
Int J Cancer
2012
;
131
:
1158
68
.
13.
Kelemen
LE
,
Cerhan
JR
,
Lim
U
,
Davis
S
,
Cozen
W
,
Schenk
M
, et al
.
Vegetables, fruit, and antioxidant-related nutrients and risk of non–Hodgkin lymphoma: a national cancer institute-surveillance, epidemiology, and end results population-based case–control study
.
Am J Clin Nutr
2006
;
83
:
1401
10
.
14.
Sabbioni
G
,
Turesky
RJ
.
Biomonitoring human albumin adducts: the past, the present, and the future
.
Chem Res Toxicol
2017
;
30
:
332
66
.
15.
Go
YM
,
Jones
DP
.
The redox proteome
.
J Biol Chem
2013
;
288
:
26512
20
.
16.
Nagumo
K
,
Tanaka
M
,
Chuang
VT
,
Setoyama
H
,
Watanabe
H
,
Yamada
N
, et al
.
Cys34-cysteinylated human serum albumin is a sensitive plasma marker in oxidative stress-related chronic diseases
.
PLoS One
2014
;
9
:
e85216
.
17.
Grigoryan
H
,
Edmands
W
,
Lu
SS
,
Yano
Y
,
Regazzoni
L
,
Iavarone
AT
, et al
.
Adductomics pipeline for untargeted analysis of modifications to Cys34 of human serum albumin
.
Anal Chem
2016
;
88
:
10504
12
.
18.
Grigoryan
H
,
Schiffman
C
,
Gunter
MJ
,
Naccarati
A
,
Polidoro
S
,
Dagnino
S
, et al
.
Cys34 adductomics links colorectal cancer with the gut microbiota and redox biology
.
Cancer Res
2019
;
79
:
6024
31
.
19.
Dagnino
S
,
Bodinier
B
,
Grigoryan
H
,
Rappaport
SM
,
Karimi
M
,
Guida
F
, et al
.
Agnostic Cys34-albumin adductomics and DNA methylation: implication of N-acetylcysteine in lung carcinogenesis years before diagnosis
.
Int J Cancer
2019
:
3294
303
.
20.
Riboli
E
,
Hunt
KJ
,
Slimani
N
,
Ferrari
P
,
Norat
T
,
Fahey
M
, et al
.
European Prospective Investigation into Cancer and Nutrition (EPIC): study populations and data collection
.
Public Health Nutr
2002
;
5
:
1113
24
.
21.
Yano
Y
,
Schiffman
C
,
Grigoryan
H
,
Hayes
J
,
Edmands
W
,
Petrick
L
, et al
.
Untargeted adductomics of newborn dried blood spots identifies modifications to human serum albumin associated with childhood leukemia
.
Leuk Res
2019
;
88
:
106268
.
22.
Grigoryan
H
,
Imani
P
,
Dudoit
S
,
Rappaport
SM
.
Extending the HSA-Cys34-adductomics pipeline to modifications at Lys525
.
Chem Res Toxicol
2021
;
34
:
2549
57
.
23.
Wong
JYY
,
Imani
P
,
Grigoryan
H
,
Bassig
BA
,
Dai
Y
,
Hu
W
, et al
.
Exposure to diesel engine exhaust and alterations to the Cys34/Lys525 adductome of human serum albumin
.
Environ Toxicol Pharmacol
2022
;
95
:
103966
.
24.
Palli
D
,
Berrino
F
,
Vineis
P
,
Tumino
R
,
Panico
S
,
Masala
G
, et al
.
A molecular epidemiology project on diet and cancer: the EPIC-Italy prospective study. Design and baseline characteristics of participants
.
Tumori
2003
;
89
:
586
93
.
25.
Chajes
V
,
Jenab
M
,
Romieu
I
,
Ferrari
P
,
Dahm
CC
,
Overvad
K
, et al
.
Plasma phospholipid fatty acid concentrations and risk of gastric adenocarcinomas in the European Prospective Investigation into Cancer and Nutrition (EPIC-EURGAST)
.
Am J Clin Nutr
2011
;
94
:
1304
13
.
26.
Huang
Y
,
Cao
D
,
Chen
Z
,
Chen
B
,
Li
J
,
Guo
J
, et al
.
Red and processed meat consumption and cancer outcomes: umbrella review
.
Food Chem
2021
;
356
:
129697
.
27.
Perttula
K
,
Edmands
WM
,
Grigoryan
H
,
Cai
X
,
Iavarone
AT
,
Gunter
MJ
, et al
.
Evaluating ultra-long-chain fatty acids as biomarkers of colorectal cancer risk
.
Cancer Epidemiol Biomarkers Prev
2016
;
25
:
1216
23
.
28.
Perttula
K
,
Schiffman
C
,
Edmands
WMB
,
Petrick
L
,
Grigoryan
H
,
Cai
X
, et al
.
Untargeted lipidomic features associated with colorectal cancer in a prospective cohort
.
BMC Cancer
2018
;
18
:
996
.
29.
He
X
,
Slupsky
CM
.
Metabolic fingerprint of dimethyl sulfone (DMSO2) in microbial-mammalian co-metabolism
.
J Proteome Res
2014
;
13
:
5281
92
.
30.
O'Keefe
SJ
.
Diet, microorganisms and their metabolites, and colon cancer
.
Nat Rev Gastroenterol Hepatol
2016
;
13
:
691
706
.
31.
Vipperla
K
,
O'Keefe
SJ
.
Diet, microbiota, and dysbiosis: a 'recipe' for colorectal cancer
.
Food Funct
2016
;
7
:
1731
40
.
32.
Brenchley
JM
,
Douek
DC
.
Microbial translocation across the GI tract
.
Annu Rev Immunol
2012
;
30
:
149
73
.
33.
Epeldegui
M
,
Hussain
SK
.
The role of microbial translocation and immune activation in AIDS-associated non–Hodgkin lymphoma pathogenesis: What have we learned?
Crit Rev Immunol
2020
;
40
:
41
51
.
34.
Paramasivan
S
,
Adav
SS
,
Ngan
SC
,
Dalan
R
,
Leow
MK
,
Ho
HH
, et al
.
Serum albumin cysteine trioxidation is a potential oxidative stress biomarker of type 2 diabetes mellitus
.
Sci Rep
2020
;
10
:
6475
.
35.
Kobayashi
Y
,
Suzuki
R
,
Yasukawa
K
,
Oba
K
,
Yamauchi
T
,
Yatomi
Y
, et al
.
Oxidized albumin in blood reflects the severity of multiple vascular complications in diabetes mellitus
.
Metabol Open
2020
;
6
:
100032
.
36.
Figueroa
SM
,
Araos
P
,
Reyes
J
,
Gravez
B
,
Barrera-Chimal
J
,
Amador
CA
.
Oxidized albumin as a mediator of kidney disease
.
Antioxidants
2021
;
10
:
404
.
37.
Alcaraz-Quiles
J
,
Casulleras
M
,
Oettl
K
,
Titos
E
,
Flores-Costa
R
,
Duran-Guell
M
, et al
.
Oxidized albumin triggers a cytokine storm in leukocytes through P38 mitogen-activated protein kinase: role in systemic inflammation in decompensated cirrhosis
.
Hepatology
2018
;
68
:
1937
52
.
38.
Oettl
K
,
Birner-Gruenberger
R
,
Spindelboeck
W
,
Stueger
HP
,
Dorn
L
,
Stadlbauer
V
, et al
.
Oxidative albumin damage in chronic liver failure: relation to albumin binding capacity, liver dysfunction and survival
.
J Hepatol
2013
;
59
:
978
83
.
39.
Nasif
WA
,
Mukhtar
MH
,
El-Emshaty
HM
,
Alwazna
AH
.
Redox state of human serum albumin and inflammatory biomarkers in hemodialysis patients with secondary hyperparathyroidism during oral calcitriol supplementation for vitamin D
.
Open Med Chem J
2018
;
12
:
98
110
.
40.
Lu
SC
.
Glutathione synthesis
.
Biochim Biophys Acta
2013
;
1830
:
3143
53
.
41.
Adamski
J
,
Suhre
K
.
Metabolomics platforms for genome wide association studies–linking the genome to the metabolome
.
Curr Opin Biotechnol
2013
;
24
:
39
47
.
42.
Dominici
S
,
Paolicchi
A
,
Lorenzini
E
,
Maellaro
E
,
Comporti
M
,
Pieri
L
, et al
.
Gamma-glutamyltransferase-dependent prooxidant reactions: a factor in multiple processes
.
Biofactors
2003
;
17
:
187
98
.
43.
Lu
SS
,
Grigoryan
H
,
Edmands
WM
,
Hu
W
,
Iavarone
AT
,
Hubbard
A
, et al
.
Profiling the serum albumin Cys34 adductome of solid fuel users in Xuanwei and Fuyuan, China
.
Environ Sci Technol
2017
;
51
:
46
57
.
44.
Aldini
G
,
Dalle-Donne
I
,
Facino
RM
,
Milzani
A
,
Carini
M
.
Intervention strategies to inhibit protein carbonylation by lipoxidation-derived reactive carbonyls
.
Med Res Rev
2007
;
27
:
817
68
.
45.
Grigoryan
H
,
Edmands
WMB
,
Lan
Q
,
Carlsson
H
,
Vermeulen
R
,
Zhang
L
, et al
.
Adductomic signatures of benzene exposure provide insights into cancer induction
.
Carcinogenesis
2018
;
39
:
661
8
.
46.
Rana
I
,
Dahlberg
S
,
Steinmaus
C
,
Zhang
L
.
Benzene exposure and non–Hodgkin lymphoma: a systematic review and meta-analysis of human studies
.
Lancet Planet Health
2021
;
5
:
e633
e43
.
47.
Vineis
P
,
Miligi
L
,
Costantini
AS
.
Exposure to solvents and risk of non–Hodgkin lymphoma: clues on putative mechanisms
.
Cancer Epidemiol Biomarkers Prev
2007
;
16
:
381
4
.
48.
Cust
AE
,
Smith
BJ
,
Chau
J
,
van der Ploeg
HP
,
Friedenreich
CM
,
Armstrong
BK
, et al
.
Validity and repeatability of the EPIC physical activity questionnaire: a validation study using accelerometers as an objective measure
.
Int J Behav Nutr Phys Act
2008
;
5
:
33
.