Abstract
Objective Amyotrophic lateral sclerosis (ALS) incidence rates are consistent with the hypothesis that ALS is a multistep process. We tested the hypothesis that carrying a large effect mutation might account for ≥1 steps through the effect of the mutation, thus leaving fewer remaining steps before ALS begins.
Methods We generated incidence data from an ALS population register in Italy (2007–2015) for which genetic analysis for C9orf72, SOD1, TARDBP, and FUS genes was performed in 82% of incident cases. As confirmation, we used data from ALS cases diagnosed in the Republic of Ireland (2006–2014). We regressed the log of age-specific incidence against the log of age with least-squares regression for the subpopulation carrying disease-associated variation in each separate gene.
Results Of the 1,077 genetically tested cases, 74 (6.9%) carried C9orf72 mutations, 20 (1.9%) had SOD1 mutations, 15 (1.4%) had TARDBP mutations, and 3 (0.3%) carried FUS mutations. In the whole population, there was a linear relationship between log incidence and log age (r2 = 0.98) with a slope estimate of 4.65 (4.37–4.95), consistent with a 6-step process. The analysis for C9orf72-mutated patients confirmed a linear relationship (r2 = 0.94) with a slope estimate of 2.22 (1.74–2.29), suggesting a 3-step process. This estimate was confirmed by data from the Irish ALS register. The slope estimate was consistent with a 2-step process for SOD1 and with a 4-step process for TARDBP.
Conclusion The identification of a reduced number of steps in patients with ALS with genetic mutations compared to those without mutations supports the idea of ALS as a multistep process and is an important advance for dissecting the pathogenic process in ALS.
Glossary
- ALS=
- amyotrophic lateral sclerosis;
- CI=
- confidence interval;
- PARALS=
- Piemonte and Valle d'Aosta Register for ALS
Amyotrophic lateral sclerosis (ALS) is a neurodegenerative disorder characterized by a progressive loss of cortical, bulbar, and spinal motor neurons, often associated with an involvement of prefrontal cortex. There are indications that the degenerative process in ALS is the consequence of a combination of genetic and environmental factors. More than 20 genes have been detected as causes of ALS.1 Several environmental factors have been proposed, but none of them, with the possible exception of cigarette smoking and military service, are consistently associated with ALS.2,–,5 About 20% of ALS heritability is attributable to common genetic variation compared with an overall heritability of 60% in studies based on concordance of monozygotic twin pairs.6,–,8
In a previous study, we used the Armitage-Doll model derived from cancer research to assess whether ALS incidence is consistent with a multistep process and, if so, to estimate the number of steps (n) required for ALS to develop.9,10 The model can be briefly conceptualized as follows: if we assume that ALS is caused in a single-step molecular process, then the incidence in a particular year will be proportional to the risk of undergoing the step, which in turn depends on exposure to the relevant disease-causing factor. The probability a second molecular step has occurred by that year is dependent on the risk of exposure to the relevant factor per year and the number of years of exposure, or age, and this is true for any subsequent step. Thus, incidence is proportional to the product of the risks of undergoing the first step and the subsequent steps. This concept implies a logarithmic increase in incidence with age, obeying a power law in which 1 less than the number of steps, n − 1, relates to the rate of increase. As a result, taking logs of the age at onset and incidence rates has the form of a straight-line equation with slope n − 1 if a multistep model applies. Our previous study found a linear relationship with a slope estimate of 5, indicating that the process leading to ALS needs on average 6 steps.9 Considering the large heterogeneity of ALS in terms of clinical presentation, progression, and outcome, it is likely that the number of steps varies in specific subgroups of patients. For example, those carrying a large effect mutation might have ≥1 steps accounted for by the effect of the mutation and thus have fewer remaining steps before ALS is established. We therefore tested this hypothesis using the Armitage-Doll model in genetically defined patient subgroups from a population-based cohort.
Methods
All people with ALS diagnosed in Piemonte and Valle d'Aosta, Italy, in the period of 2007 to 2015 were eligible to be enrolled in the study. Cases were identified through the Piemonte and Valle d'Aosta Register for ALS (PARALS). PARALS is a prospective epidemiologic register based on the collaboration of the neurologic departments of the 2 Italian regions. ALS cases are ascertained through several concurrent sources (hospital admission, etc.). ALS diagnosis is based on El Escorial revised criteria. Cases with definite, probable, and probable laboratory-supported El Escorial diagnosis during the course of the disease are included in the register. A detailed description of register methodology is reported elsewhere.11 The cohort included in this study is different from that included in the previous one, which was based on patients incident in the 1995–2004 period.
As a confirmation cohort, we used the data from ALS cases diagnosed in the Republic of Ireland in the 2006–2014 period. ALS cases were identified though the Irish ALS register.12 Although similar cohorts exist for the other registers studied in our original report, the genetic data either are not complete enough or do not overlap enough with the population data to allow similar analysis.
Genetic analysis
All cases were tested for mutations in SOD1 (all exons), TARDBP (exon 6), FUS (exons 14 and 15), and C9orf72 with the use of standard methodology described elsewhere.13 C9orf72 repeat length was determined with repeat primed PCR. Normal was defined as ≤28 repeats.
Statistical analysis
The Armitage-Doll methodology was used,10 under the same assumptions as our previous report.9 In brief, a plot of the log of ALS incidence against log age will be linear if a multistep model applies and will have slope n − 1, i.e., 1 less than the number of steps needed for disease onset. According to the pattern identified in cancer, the model predicts that the slope will be approximately linear but will decrease (and therefore will be less than linear) at older age groups due to a substantial proportion of the population having undergone 1 or more of the earlier steps.
Following this model, we calculated the incidence rates per 100,000 person-years in 5-year age groups for people 35 to 74 years of age. We excluded the youngest age groups (those <35 years) because of the small number of patients and the older age groups (those >74 years) because of the risk of underascertainment or cohort effect; this reflects also the finding in some cancers for which the log incidence and log age association is nonlinear in the older age groups.10
We then performed a preliminary analysis of the log incidence against log age on all cases (i.e., both mutated and nonmutated) to verify whether our population followed a multistep model and to replicate our previous findings. Second, we assessed separately patients with familial and those with nonfamilial ALS. Third, we assessed the incidence of ALS for cases involving each single gene. To correctly calculate incidence, the population used for the denominator should correspond to the population used for the numerator. For example, for ALS incidence in those carrying a C9orf72 mutation, the correct denominator to use would be the count of all people in the population carrying a C9orf72 mutation. This information was available only for the cases but not for the general population. However, because the relevant mutations do not in general markedly increase mortality apart from their effects on ALS, we assumed that the proportions of the population carrying a specific mutation would not differ substantially by age group (e.g., the proportions with the C9orf72 mutation would be similar in the 40- to 44- and 60- to 64-year age groups). Under this assumption, it is then reasonable to use the total population as the denominators in the analyses for specific genes (e.g., cases involving the C9orf72 mutation) because this would involve multiplying the relevant age-specific population denominator by an unknown but fixed constant (e.g., if 5% of the population carry a particular mutation, then the total population denominator would be 20 times that of the unknown population subgroup carrying this mutation). Thus, all of the age-specific incidence rates would be overestimated by an unknown but fixed multiplying factor; this in turn would affect the age-specific incidence rates but would have no effect on the slope of the graph of log incidence against log age.
Standard protocol approvals, registrations, and patient consents
The Piedmont regional government has recognized the Piemonte ALS Registry as a Registry of High Sanitary Interest (regional law, April 11, 2012, No. 4). Accordingly, PARALS has the right to access all the existing databases owned by the regional administration and to obtain clinical information about patients with ALS from public and private hospitals and general practitioners. The study was approved by the ethics committee of the Città della Salute e della Scienza of Turin. The register database is anonymized and treated according to Italian Data Protection Code. Patients sign a written informed consent. The Irish ALS Register complies with Irish Data protection legislation (1988 and 2003) and has been approved by the Beaumont Hospital Ethics Committee (02/28 and 05/49).
Data availability
Anonymized data will be shared by request from any qualified investigator.
Results
Of the 1,309 cases incident during the 2007–2015 period, 1,077 (82.2%) underwent genetic analysis of all 4 genes, 93.5% (1,030) of those followed up by the 2 ALS multidisciplinary centers and 21.7% (47) of those followed up by general neurology departments. Patients who did not undergo genetic analysis were older and more frequently had a bulbar onset than those who were tested (table 1). C9orf72 mutations were detected in 74 cases (6.9%), SOD1 in 20 (1.9%), TARDBP in 15 (1.4%), and FUS in 3 (0.3%). One patient carried both a C9orf72 expansion and the p.Asn390Ser heterozygous missense mutation of the TARDBP gene. A list of SOD1, TARDBP, and FUS mutations is reported in table 2.
Comparison of patients with ALS who underwent genetic assessment vs patients who were not assessed
List of missense genetic mutations of SOD1, TARDBP, and FUS genes
In the 1,077 patients with genetic test data, there was a linear relationship between log incidence and log age (r2 = 0.98) with a slope estimate of 4.65 (95% confidence interval [CI] 4.37–4.95), consistent with a 6-step process (figure 1A), replicating our previous findings. A similar result (r2 = 0.99) was obtained when all 1,309 incident cases (figure 1B) were included. There was no effect of sex (data not shown).
(A) Log incidence vs log age for all patients with incident amyotrophic lateral sclerosis (ALS) who have been genetically tested (n = 1,077) (y = 4.65x − 7.60, r2 = 0.98). (B) Log incidence vs log age for all patients with incident ALS in the register (n = 1,309) (y = 4.83x − 7.85, r2 = 0.99).
When the 109 patients with definite or probable familial ALS (10.1% of the total) were considered,14 there was a linear relationship between log incidence and log age, with a slope estimate of 2.95 (95% CI 2.43–3.57), consistent with a 4-step process (figure 2).
Log incidence vs log age for all patients with incident familial amyotrophic lateral sclerosis (ALS) (n = 111) (y = 2.95x − 5.45, r2 = 0.92).
The analysis for C9orf72-mutated patients confirmed a linear relationship (r2 = 0.94) with a slope estimate of 2.22 (95% CI 1.74–2.79), suggesting a 3-step process (figure 3A). Similarly, a linear relationship was found for SOD1-mutated patients (r2 = 0.53, n − 1 = 0.76, 95% CI 0.46–1.17), consistent with a 2-step process (figure 3B), and for TARDBP (r2 = 0.93, n − 1 = 3.24, 95% CI 2.21–4.13), consistent with a 4-step process (figure 3C). Because of the very small number of cases carrying FUS mutations, we did not estimate the slope. When we considered the 45 patients with familial ALS who were negative for the 4 tested genes, the linear relationship was confirmed (r2 = 0.95, n − 1 = 3.71, 95% CI 2.67–4.53), consistent with a 5-step process (figure not shown). These data are summarized in table 3.
Log incidence vs log age for C9orf72 amyotrophic lateral sclerosis (ALS) (74 cases) (y = 2.22x − 4.33, r2 = 0.94) (red line), for SOD1 ALS (20 cases) (y = 0.758x − 2.43, r2 = 0.53) (green line), and for TARDBP ALS (15 cases) (y = 3.24x − 6.76, r2 = 0.93) (blue line). The fit to a straight line is good, consistent with a multistep model.
Comparison of log incidence vs log age for different ALS subgroups
We next analyzed patients from the Irish ALS register. The register includes 597 genetically tested patients (56.3% of incident patients in the 2006–2014 period), of whom 67 carried a C9orf72 expansion. In the 597 patients with genetic test data, there was a linear relationship between log incidence and log age (r2 = 0.93) with a slope estimate of 5.09 (95% CI 4.69–5.52), consistent with a 6-step process. In the C9orf72-expanded cases, results were similar to those of the Piemonte register (r2 = 0.66, slope estimate 2.47, 95% CI 1.91–3.13, consistent with a 3-step process). Finally, the 530 Irish patients without a C9orf72 expansion had a slope estimate of 5.35 (95% CI 4.92–5.82) (r2 = 0.95). No patients with SOD1 mutations and only 2 with TARDBP missense mutations were identified in the Irish ALS register, making it impossible to assess the effects of these genes.
For comparison, we assessed the slope for type 1 and 2 diabetes mellitus using data from the Piemonte register for diabetes mellitus for the 30- to 49-year age groups (figure 4).15 In keeping with our findings on ALS, the slope estimate for type 1 diabetes mellitus, a highly genetically determined disease, was 0.96 (95% CI 0.62–1.13) (r2 = 1.0), consistent with a 2-step process, while that of type 2 diabetes mellitus, a multifactorial disease with a polygenic architecture, was 5.27 (95% CI 4.50–6.18) (r2 = 0.98), consistent with a 6-step process.
Data from Piemonte diabetes register.14 Log incidence vs log age for type 1 diabetes mellitus (y = 0.96x − 0.66, r2 = 0.98) (red line) and type 2 diabetes mellitus (y = 5.28x − 6.78, r2 = 1.0) (blue line).
Discussion
We have found that in patients carrying a genetic mutation, the slope of the graph of log incidence and log age is lower than that of cases who do not carry these mutations. This in turn implies that the number of steps necessary to start the neurodegenerative process in genetically mediated ALS is reduced compared to cases without mutation. The number of steps varies according to the mutated gene and is lower for SOD1 (2), intermediate for C9orf72 (3), and higher for TARDBP (4). The number of steps identified in patients without mutation is 6, consistent with our previous report.9 In particular, the slope in the patients from the Piemonte register reported in that article, which was based on incident cases in the 1995–2004 period, is almost identical to that found in the present report, which was based on the incident cases in the 2007–2015 period. Furthermore, the slope for C9orf72, as well as the overall slope of genetically tested patients, was confirmed in the Irish ALS population. These findings suggest that a genetic lesion alone might account for up to 4 molecular steps, leaving only 2 further, likely environmental, steps for those with SOD1 mutation, for example. This argues for the concentration of efforts in dissecting environmental risk factors in individuals with identified mutations rather than those with apparently sporadic ALS, because such environmental factors will be fewer in number per person and likely of larger effect size as a result.
It is generally recognized that ALS is a multifactorial disease, characterized by interplay between genetic and environmental factors. Although several ALS-related genes are known, it is increasingly clear that genetic mutations alone cannot fully explain the pathologic process in ALS but rather that genes can be considered triggers of the degenerative process. A similar role can be attributed to environmental toxins. However, we have very little information about the possible exogenous factors involved in ALS. Cigarette smoking may be a risk factor in ALS5,16; other suggested factors are physical activity, participating in professional sports, and physical trauma.4 Protective factors have also been hypothesized such as diabetes mellitus17 and an unfavorable lipid profile.18,19 All these factors could act on the genome through epigenomic interactions. For example, smoking induces DNA hypermethylation in specific CpG sites, which persists for years after cessation of smoking,20 or may induce somatic nucleic acid changes.5,21 It is likely that the remaining steps in different genetic subgroups may originate from 1 or more of these risk factors.
Besides our current results, more observations fit the multistep hypothesis in ALS. First, there are indications that ALS can be an oligogenic disease. In fact, there are several reports of patients carrying ≥2 mutations of different ALS-related genes.22 In a study of 391 patients with ALS that assessed variants in 17 genes, 3.8% had variants in >1 gene.23 In that series, the burden of rare variants in known ALS genes significantly reduced the age at onset of symptoms.23,24 In the present series, 1 patient had both a C9orf72 expansion and a heterozygous mutation of the TARDBP gene, even though we assessed only 4 genes. Second, besides “causative” genes, several other genes have been reported to modify ALS phenotype such as UNC13A, ATXN2, and CAMTA1,25,–,27 suggesting that variants in these genes modify the sequential process, either accelerating or slowing it.
Nongenetic elements such as environmental factors28 and aging also likely trigger molecular steps. However, consistent with other reports, the slope is the same between sexes in all analyses, suggesting that there is no effect of sex on the assumed cascade.29
There appears to be some relationship between the number of remaining steps identified for each mutated gene and the penetrance of mutation in the gene. Such a relationship is consistent with a multistep model because a greater number of remaining steps will correspond to a lower probability of exposure to all the steps and therefore reduce the probability of disease given a specific genotype. For example, C9orf72 expansion mutation penetrance has been estimated to be 60% at the age of 60 years and 91% at the age of 80 years30,31 and corresponds to 3 remaining steps. At least 3 mechanisms might regulate C9orf72 penetrance: the size of the GGGGCC expansion, DNA methylation and transcriptional downregulation of the promoter,32 and the presence of additional mutations.33
The penetrance of TARDBP mutation is much lower than that of C9orf72 (60% at 80 years for the p.Ala382Thr mutation),34 and it leaves 4 remaining steps, more than for the other 2 genes. The lowest number of remaining steps, 2, has been estimated for SOD1 mutation. However, SOD1 penetrance varies across the different mutations. For example, in a study on pedigrees dating back to the 18th century, carriers of p.Glu101Gly, p.Ile114Thr, and p.Val149Gly SOD1 mutations were reported to have a penetrance of >95% at the age of 78 years.35 Similarly, the penetrance of the p.Ala5Val mutation, the commonest in the United States, has been estimated to be 91% at the age of 80 years.36 Other mutations have a much reduced penetrance; an example is the p.Asp91Ala mutation, which is transmitted with a recessive inheritance in people of Scandinavian ancestry and with a dominant inheritance, albeit with a low penetrance, in the other populations.37,38 Most of the SOD1 mutations we identified are regarded as having very high penetrance and would therefore be expected to account for more steps than low penetrance mutations.
This study has some weaknesses. First, it was not possible to genotype all patients with incident ALS. Nontested patients were older and more frequently had bulbar onset than those who were tested. However, we could obtain DNA for >80% of incident patients, a high proportion in an epidemiologic setting. Second, only the 4 more commonly mutated ALS genes were assessed. However, nontested genes account for only a fraction of patients with ALS in European-derived populations. Third, the estimation of the slope was performed on the relatively small number of genetic cases, in particular for SOD1 and TARDBP; therefore, the slope estimates may be imprecise. Finally, population denominators were not available for specific mutations; however, as noted above, this would have affected our age-specific incidence estimates but not the slope of the graph of log incidence against log age. It is therefore important that our findings be replicated in other populations with larger cohorts of patients to confirm our results and to determine the extent to which they can be generalized.
The identification of a reduced number of steps in patients with ALS with genetic mutations compared to those without mutations strongly supports the idea of ALS as a multistep process and represents a first clue for uncovering the pathogenic process of ALS. Similar patterns have previously been observed in studies of specific cancers in which the relevant mutations and other environmentally induced steps have been able to be identified and postulated as also being relevant to neurodegeneration.21 Our findings support the idea of parallels between the processes leading to carcinogenesis and those leading to ALS. The fact that only 2, 3, or 4 steps are required before disease onset in genetically mediated ALS is consistent with the concept that up to 4 of the 6 steps required for disease onset are already accounted for by inherited mutation. This idea is also consistent with the observation that penetrance corresponds to the number of steps accounted for. An alternative explanation is that the underlying etiology must differ in at least 1 step between genetic and other forms of ALS. An analysis of the influence of nongenetic risk factors should therefore also be performed to clarify their contribution to the multistep process of ALS. The relatively limited number of steps leading to ALS, compared, for example, to the complexity of the mechanisms at the base of other multifactorial diseases such as schizophrenia,39 provides hope for the development of an effective therapy for this devastating disease.
Author contributions
A. Chiò, L.M., J.H.V., L.H.v.d.B., N.P., O.H., J.R, G.M., A. Calvo, and A.A.-C. contributed to the literature search, figures, study design, data collection, data analysis, data interpretation, and writing the manuscript. S.D., A. Canosa, C.M., U.M., E.B., L.C., M.B., M.B., W.S., R.M., and A.V. contributed to the data collection and data analysis. All authors critically revised the manuscript.
Study funding
This study has been supported by the Italian Ministry of University under the Department of Excellence funding awarded to the “Rita Levi Montalcini” Department of Neuroscience. This is an EU Joint Programme–Neurodegenerative Disease Research (JPND) project. The project is supported through the following funding organizations under the aegis of JPND: UK: Medical Research Council (MR/L501529/1; MR/R024804/1) and Economic and Social Research Council (ES/L008238/1); Ireland: Health Research Board; Netherlands: ZonMw; and Italy: Ministry of Health and Ministry of Education, University and Research. The work leading up to this publication was funded by the European Community's Health Seventh Framework Programme (FP7/2007–2013; grant agreement 259867). O.H. and J.R. are funded by grants from the Irish Health Research Board and by the charity Research Motor Neurone. A.A.-C. receives salary support from the National Institute for Health Research Maudsley Biomedical Research Centre.
Disclosure
A. Chiò reports grants from the Italian Ministry of Health (Ricerca Finalizzata), EU JPND through the Ministry of Education, University, and Research, and the Italy-Israel Scientific Collaboration through the Italian Foreign Ministry, as well as personal fees from Biogen Idec, Cytokinetics, Italfarmaco, Mitsubishi Tanabe, and Neuraltus. L. Mazzini reports no disclosures relevant to the manuscript. S. D'Alfonso reports a grant from Agenzia Italiana per la Ricerca sulla SLA. L. Corrado and A. Canosa report no disclosures relevant to the manuscript. C. Moglia reports grants from the Italian Ministry of Health (Ricerca Finalizzata) and Compagnia di San Paolo. U. Manera, E. Bersano, M. Brunetti, M. Barberis, and J. Veldink report no disclosures relevant to the manuscript. L. van den Berg reports grants from The Netherlands ALS Foundation, Netherlands Organisation for Health Research and Development (Vici scheme), VSB fonds, H. Kersten and M. Kersten (Kersten Foundation), Prinses Beatrix Fonds (PB 0703), Adessium Foundation, and Netherlands Organisation for Health Research through the JPND; personal fees from travel grants and consultancy fees from Baxter; and personal fees from Scientific Advisory Board Biogen Idec. N. Pearce, W. Sproviero, R. McLaughlin, A. Vajda, O. Hardiman, and J. Rooney report no disclosures relevant to the manuscript. G. Mora reports grants from Italian Ministry of Health (Ricerca Finalizzata). A. Calvo reports no disclosures relevant to the manuscript. A. Al-Chalabi reports grants from the EU JPND through the Medical Research Council and the Economic and Social Research Council, as well as consultancy for Biogen Idec, Cytokinetics Inc, Treeway Inc, Mitsubishi-Tanabe Pharma, and OrionPharma. Go to Neurology.org/N for full disclosures.
Footnotes
Go to Neurology.org/N for full disclosures. Funding information and disclosures deemed relevant by the authors, if any, are provided at the end of the article.
The Article Processing Charge was funded by Research Councils UK.
- Received December 3, 2017.
- Accepted in final form May 16, 2018.
- Copyright © 2018 The Author(s). Published by Wolters Kluwer Health, Inc. on behalf of the American Academy of Neurology.
This is an open access article distributed under the terms of the Creative Commons Attribution License 4.0 (CC BY), which permits unrestricted use, distribution, and reproduction in any medium, provided the original work is properly cited.
References
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